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Executive Compensation-Implied CEO Risk-Taking and Systemic Risk
of Bank Holding Companies
G. Nathan Dong 1 Columbia University
May 27th, 2018
ABSTRACT
When a manager accepts the offer of employment to become the CEO of the firm, his
compensation contract that is supposedly intended to maximize the value of the firm and his
personal utility reveals the risk preference of this new CEO. Assuming the observed executive
compensation implements best effort and the compensation contract is optimal; the principal-
agent model is fitted to show a relatively high level of risk-taking among CEOs in the United
States. Both the non-firm wealth of the CEOs and the moneyness of their option holdings are
negatively related to their implied risk-aversion. Across industries, CEOs in wholesale trade are,
on the average, the most risk-averse, whereas financial institutions rank fourth behind those in
retail trade, construction, and agriculture industries in terms of risk-taking. More importantly,
the relation between the degree of risk-taking of a bank CEO and the amount of systemic risk
that the bank contributes to the entire financial system is very weak.
Keywords: CEO compensation, risk taking, systemic risk, bank holding companies
JEL Classification: G20, G21, D86, J33
1 Assistant Professor of Financial Management, Department of Health Policy and Management, Columbia University. 722 West 168th Street, New York, NY, USA. Tel: 1-212-342-0490. E-mail: [email protected]. We thank Craig Brown, Ruediger Fahlenbrach, Steve Kou, and participants in the National University of Singapore (NUS) Annual Risk Management Conference, Portsmouth-Fordham Conference on Banking and Finance, The Second Shanghai Risk Forum (SHUFE). All errors remain our responsibility.
2
“In recent years, anti-regulatory ideology kept the United States from modernizing the rules of the capitalist game in a period of intense financial innovation and perverse incentives to creep in.”
― Alice Rivlin’s Testimony before the House Committee on Financial Service, July 21, 20092
“Shareholders’ interest in more risk-taking implies that they could benefit from providing executives with excessive incentives in this direction. Executives with such incentives can use their informational advantages, and whatever discretion they have been left by existing regulations, to increase risks.”
― Financial Times, August 3, 20093
I. Introduction
Despite a large body of studies on estimating the distribution of individuals’ risk preferences in
various settings, prior literature of inferring the degree of risk aversion (or concavity of
marginal utility) of decision makers such as corporate executives is scarce, and little research
has been done to examine the link between an executive’s risk preference and the characteristics
of both the manager and the company. Senior executives play a critical role in not only
formulating business strategy and ensuring operational efficiency but also answering for
financial performance to the shareholders. Understanding the heterogeneity of their risk
preferences is important in order to link risk-taking incentives embedded in executive
compensation contracts to managerial and strategic decisions, such as altering capital structure,
hoarding cash, allocating capital investments, manipulating accounting numbers, and
committing financial fraud. Therefore, the question of whether senior executives of publicly
traded companies exhibit high or low degree of risk aversion becomes a relevant concern and
has not been conclusively resolved. More importantly, in the banking sector, financial
innovations such as securitization with which bank assets (mainly mortgages) can be easily sold
to other investors offer financial services firms the advantage of reduced cost of asset sales that
eventually causes higher levels of risky lending (Santomero and Trester 1998). The public anger
over the executive compensation at financial firms–coupled with common beliefs that
compensation-induced excessive risk-taking was the root cause of the 2008-10 financial crisis
(see the quotes above 4)–led to the question of whether top executives of financial services firms
2 Excerpt from Rivlin (2009). 3 Except from Bebchuk (2009). 4 For the detailed discussion of this issue in EU countries, see Murphy (2013).
3
actually responded to compensation incentives to take excessive risks that eventually led to the
crisis.
The main challenge to answer this question lies in the fact that it is difficult, if not
possible, to quantify or measure risk preferences of corporate executives in a laboratory setting.
Even a controlled experiment is conducted it is very likely that their risky choice in the lab
situation does not resemble the decision-making behavior they might display in the real-world
business environment. In this paper, we propose a calibration method to recover risk-aversion
measures of corporate executives from their observed compensation contracts. It is well known
that individuals with different degrees of risk aversion choose different types of contracts
(Ackerberg and Botticini 2002; Allen and Lueck 1995). In the context of executive compensation
design, the decision that a manager serves as CEO of the firm and receives compensation in the
form of stock and options is materially affected by the interaction of risk preference and
compensation structure (e.g., cash salary, stock and options). On the one hand, CEOs with a
certain level of risk-aversion choose to work for firms offering compensation contracts with
embedded risk profiles that match those of CEOs, and on the other hand, holding executive
stock and options may increase or decrease managerial risk taking, as illustrated theoretically
by Ross (2004) and empirically by Lewellen (2006), among others. In equilibrium, the
compensation contract maximizes the firm value and the CEO’s utility, and the observed
contract implements the CEO’s optimal action. Therefore, fitting the standard principal-agent
model using observed executive compensation contracts can reveal the CEOs’ risk preferences.
This research contributes to existing evidence on estimating the implied risk aversion
and relating the degree of risk-taking of bank CEOs to the level of systemic risk (i.e., the amount
of risk that each individual bank contributes to the entire financial system). There is a
voluminous literature on option-implied risk preferences, surveyed by Bliss and Panigirtzoglou
(2002). For example, risk preferences can be estimated by applying the semi-parametric method
of Aït-Sahalia and Lo (1998, 2000) for estimation of the option-implied density function in two
steps. The first step estimates implied strike prices from the deltas as a smooth function,
following Bliss and Panigirtzoglou (2004) and Kang and Kim (2006), and the second step plugs
the GBS volatility function in a lognormal density. As a final step, the Aït-Sahalia and Lo
estimator yields relative risk aversion and marginal rate of substitution, both depending on the
stock price. However, this type of estimation method only produces firm-level risk preference,
4
and unfortunately, it offers little help in understanding the degree of risk-aversion on the CEO
level. These issues are in focus after the introduction of accounting standards IFRS 2 (see
International Accounting Standards Board, 2004), SAB 107, and FAS 123R (see Securities and
Exchange Commission, 2005), and the Dodd-Frank Wall Street Reform and Consumer
Protection Act (see Securities and Exchange Commission, 2015), requiring publicly traded firms
to expense the value of executive stock options and to disclose the ratio of the CEO
compensation to the median compensation of its employees. In contrast to common practice,
this paper extends the principal-agent models of Holmstrom (1979), Dittmann and Maug (2007),
and Armstrong, Larcker and Su (2007) and calibrate the model with observed cash salary, stock
and options in executive compensation contracts to estimate the risk-aversion of individual
CEOs. As the first paper to address the question if executive compensation contributed to the
financial crisis, Fahlenbrach and Stulz (2011) find no evidence that banks with CEOs whose
incentives were better aligned with the interests of their shareholders performed better during
the crisis. Also evidence indicates that these banks actually performed worse. Banks whose
CEOs had better incentives in terms of the dollar value of their stake in the company performed
significantly worse than banks where CEOs had poorer incentives. This implies that incentive
compensation had no adverse impact on bank performance during the crisis. While many of the
bank CEOs made high cost, bad bets that cost themselves and their shareholders, the data
suggests that CEOs took these bets because they believed they would be profitable for the
shareholders. On the contrary, Bennett, Guntay and Unal (2012) show that banks with CEOs
holding more inside-debt relative to equity in 2006, experienced higher default risk and lower
stock returns in 2008.
The closest paper to our risk-aversion estimation approach is Brenner (2015), who
estimates the risk preferences of U.S. executives from data on the exercising of employee stock
options. Its calibration method makes use of the assumption that these senior corporate
managers (as option holders) choose the stock prices at which to exercise the options such as to
maximize their subjective value. Such approach has the advantage of relying on a simplistic
argument over the optimal choice of the share price that triggers the option exercise to identify
the risk preferences, while our approach requires a condition of “optional contract”, meaning
the executive would only be offered a contract of employment to serve as the CEO of the firm if
the compensation reflected the optimal level of efforts that the CEO-elect would exert in order
5
to maximize the firm value. Nonetheless, our calibration result of the average Arrow-Pratt
measure of relative risk-aversion being 4.6 for 290 long-serving CEOs in the United States, to
some extent, is consistent with the finding in Brenner (2015) that senior executives are more risk
taking than managers of lower rank. What is more interesting in our study is that the mean
level of risk aversion of American CEOs remains stable (between 4.2 to 5.5) over a long period
of time from 1997 to 2013, as shown in Figure 1, except a slight fluctuation between 2004 and
2006. However, the box plot of upper adjacent value, 75th percentile, median, 25th percentile,
and lower adjacent values presents a slightly different picture: the distribution changes
dramatically over time and since 2001, the median level of risk-aversion has been gradually
declining, with some fluctuations, and reached the lowest level in 2005 and 2006 before
bouncing back again in 2007 and 2008. To some extent, this evidence may support the argument
that excessive risk-taking was a major contributing factor of the recent financial crisis of 2008-
2010, at least on the aggregate; however, when we actually use two measures of systemic risk
that proxy for the amount of risk that an individual bank contribute to the entire financial
system (SES and CoVaR),5 the relationship between bank CEO risk-aversion and systemic risk
vanishes.
[Insert Figure 1 Here]
The remainder of the paper is organized as follows. Section II reviews the relevant prior
research. Section III specifies the theoretical model and empirical method in detail. Section IV
describes the sample data. Section V presents empirical results. Section VI discusses the
implication and concludes.
II. Related Literature
This paper is related to four strands of literature. The first set of related studies provide some
evidence on the risk preferences of executives, for example, Grahama, Harvey and Puri (2013)
for privately held firms. In a more recent study, Cain and McKeon (2016) use the possession of a
FAA (Federal Aviation Administration) pilot license and living near a major airport to identify
risk-seekers among executives and find that risk-seeking pilot CEOs engage in more
acquisitions that eventually lead to positive value creation. Corporate senior executives
represent a demographic group that is often associated with a very special set of socioeconomic
5 SES (Acharya et al. 2016) in and CoVaR (Adrian and Brunnermeier 2016).
6
characteristics and psychological traits (e.g., Harvard dropout, Marine Corps veteran), all of
which may correlate with risk preferences. On the one hand, they often invested in human and
social capital during their early careers that allow them to be competitive and entrepreneurial,
and the propensity to make such investments is related to risk aversion (Shaw 1996), and on the
other hand, the selection of CEOs is generally on the basis of merit and competitive examination
and Skaperdas and Gan (1995) argue that the probability of becoming a CEO after a
comprehensive selection process may itself be a function of risk aversion. Therefore, it is often
not feasible to extrapolate from studies of risk aversion from non-executives data (Borghans,
Lex, James Heckman, Bart Golsteyn, and Huub Meijers 2009; Dohmen, Falk, Huffmann and
Sunde 2010; MacCrimmon and Wehrung 1990).
Second, starting with an influential paper by Jensen and Meckling (1976), a literature in
finance attempts to explain to what extent equity-based compensation contracts induce
managerial risk taking. Later on, Carpenter (2000) and Ross (2004) argue the inducing effect of
options based compensation on risk taking depends on the manager’s utility function, because
increasing the wealth of the executive may move into more or less risk-averse portions of the
utility function. Concentrating on volatility costs of debt, Lewellen (2006) finds that managers
holding in-the-money options are typically worse off by an increase in leverage, based on
certainty equivalent of wealth. Lambert, Larcker and Verrecchia (1991) suggests that the
managerial incentives provided by compensation contracts do not necessarily follow from the
application of market-based valuation formulas. Hall and Murphy (2002) estimates options
values using “certainty equivalence” approach, similar to Lambert, Larcker and Verrecchia
(1991), and claim that granting at-the-money options maximizes incentives when grants are an
add-on to existing pay packages, while restricted stock is preferred when grants are
accompanied by reductions in cash compensation. Meulbroek (2001) provides empirical
evidences that managers value stock or option-based compensation at less than its market value,
because undiversified managers are exposed to the firm’s total risk but rewarded for the
systematic risk. Kadan and Swinkels (2008) find that options can dominate stocks as a means of
motivation only if default risk is not substantial, regardless of the exiting portfolio of the
manager. Aseff and Santos (2005) explain why most stock options are granted at the money
using the intermediate role of the strike price, and in turn suggest that a relatively small
7
additional cost to the principal in compensation such as the use of simple stock options can
incentivize the agent to exert high effort.
A third related literature use calibration technique of option pricing models, such as by
eliciting subjective option values from calibrating utility models to observed exercise pattern by
employees (e.g., Ingersoll 2006; Bettis, Bizjak and Lemmon 2005). A small subset of these studies
ask if the observed compensation contract reflects the optimal level of the CEO’s effort, we can
actually find another contract, with a new mix of salary, stock and options, which will cost less
to the firm. In a typical principal-agent model, to maximize financial returns, the principal has
to incentivize the agent to exert the optimal level of effort and in turn take the appropriate
amount of risk (Holmstrom and Milgrom 1987). However, the difficulty to find an optimal
managerial compensation contract lies in the fact that we cannot quantify the optimal level of
the CEO’s effort. Dittmann and Maug (2007) assume the observed compensation contracts
implement the optimal action, meaning the beginning stock price anticipates the optimal effort
that will be selected by the agent for a given compensation contract. This assumption simplifies
the classical principal-agent problem to a principal-only problem. Their model predicts that
optimal compensation schemes should have no or at best miniscule holdings of stock options,
and incentives should be provided through restricted stock. Finally, Armstrong, Larcker and Su
(2007) avoid the use of first order approach as in Dittmann and Maug (2007) and reach the exact
opposite conclusion that stock options are an important part of the optimal CEO compensation
contact.
Most of these papers do not calibrate a principal-agent model explicitly to back out
the CEO’s managerial risk aversion. This paper takes a step further and proposes a new
numerical calibration approach to back out the degree of managerial risk preference by
assuming not only the optimal effort but also the optimal contract, meaning that the observed
executive compensation has already attained the level at the lowest cost to the firm. In previous
studies, Hall and Murphy (2000) and Hall and Murphy (2002) use assumed risk aversion
coefficients, because empirical estimates are few and exhibit significant variation. This paper
contributes to the literature by estimating relative risk-aversion based on executive
compensation data including cash-based salary, stock and options.
Of course, this paper is also closely related to the literature on systemic risk. The
contagion effect of an event usually refers to the spillover effects of stocks of one or more firms
8
to others (Kaufman 1994), but has also been characterized as the change in the value of a firm
that can be attributed to economic events with a clearer and more direct impact on some other
firm (Docking, Scott, Hirschey, and Jones 1997). Contagion has been studied widely in the
theoretical and empirical financial literature (for reviews see Flannery 1998). The focus of
analysis has ranged from strong systemic shocks involving multiple bank failures, currency
crises, and market crashes to informational spillover effects that lead to the revaluation of stock
prices but not to widespread failures. This paper contributes to this body of literature by
connecting a bank CEO’s risk-taking propensity to the amount of risk that a bank contributes to
the stability of the entire financial system. To do so we we use the CoVaR measure developed
by Adrian and Brunnermeier (2016) and the Systemic Expected Shortfall (SES) measure in
Acharya et al. (2016) to measure systemic risk.
III. Numerical and Empirical Methods
We assume that the traditional moral hazard model is an appropriate representation of the
contracting problem involving principal and agent. My model is based on a traditional single
period agency setting with a risk-neutral principal (i.e., the representative shareholder in theory
and the board of directors in reality) and a risk-averse and effort-averse agent (i.e., the CEO).
The CEO has an additively separable utility function (CRRA) defined over terminal wealth, the
sum of the initial wealth compounded at risk-free rate in one period and the current period
compensation:
1
( )1T
T
WU W
, γ ≠ 1
( ) ln( )T TU W W , γ = 1
The CEO’s disutility of the effort, D(e), is a convex and monotonic increasing function of
effort e. The CEO selects the effort level to maximize the expected utility of terminal wealth less
the disutility. It is assumed that CEO’s choice of effort satisfy the incentive compatibility (IC)
constraint.
The risk-neutral principal selects a compensation contract to maximize the expected
value of the firm net of the expected compensation to the CEO. We assume that the
compensation contains only cash (salary and bonus), restricted stock and stock options, and the
principal decides the allocation of the compensation among these types. We require the
9
minimum payment (MP) constraint or limited liability, meaning the cash compensation is
greater than or equal to zero. This is consistent with Armstrong, Larcker and Su (2007). It is not
a trivial constraint, and it has serious impact on the result of this non-linear optimization
problem that we. Dittmann and Maug (2007) allow cash compensation bounded below at CEO’s
negative initial wealth: 0W . Their result has negative cash compensation and zero weight
in options, and they in turn argue for all restricted stock grants as optimal compensation.
Without the limited liability constraint, the CEOs are forced to invest all their wealth to their
company stocks. This is like replicating stock options in discrete time using delta number of
stocks.
The no-shorting (NS) constraint is that the number of stock and the number of options
are positive and the total shares (TS) constraint is that the total number of stocks and options is
less than total shares outstanding. It is further assumed that the compensation satisfies the
individual rationality (IR) constraint that the expected utility from this compensation contract
less the cost of effort is greater than or equal to the utility of the reservation wage that the CEO
can earn in the outside the executive labor market.
The basic principal’s problem is defined as follows. The principal (shareholders)
maximizes expected profit, measured as total market value of equity net of compensation paid
to the agent (CEO) subject to incentive compatibility (IC) and participation constraint (IR):
1 21 2
, , ,[ ( max( ,0)) | ]T T T
eMax E NP P P K e
s.t. 0 1 2arg max{ [ (( ) max( ,0)) | ] ( )}fr T
T Te
e E U W e P P K e D e
(IC)
0 1 2[ (( ) max( ,0)) | ] ( )fr T
T TE U W e P P K e D e U (IR)
0 (MP)
1 20, 0 (NS)
1 2 N (TS)
N is the total number of shares outstanding. α is the cash compensation including salary
and bonus. β1 is the number of restricted stocks granted to the CEO. β2 is the number of stock
options granted to the CEO with strike price K. W0 is CEO’s initial wealth. D(e) is the CEO’s
disutility of action or effort, e, and U is the CEO’s reservation utility. PT is the terminal stock
price at time 1, and its distribution is lognormal: 2
( )2
0
fr T u T
TP P e
, where (0,1)u N .
10
Without any assumption of disutility function D(e), the implementation of the model depends
on first-order approach which replaces the (IC) constraint with the respective first-order
condition for utility maximization by the CEO, by assuming observed compensation contracts
imply optimal actions of CEOs. Following the definition of utility-adjusted pay-for-performance
sensitivity in Dittmann and Maug (2007):
0 1 2( ) max( ,0)fr T
T T TW W e P P K
The first order condition of the IC constraint: arg max{ [ ( ) ( )}Te
e E U W D e
is:
0
0
( ) ( )[ ] 0T dPdU W dU dD eE
de dP de de
UPPS is defined as:
0 0
0 0
( ) ( )( )[ ] [ ]f fr T r TT TT
TT
dW P dW PdU WUPPS e E e E W
dW dP dP
UPPS depends only on the observable compensation contract parameters including WT
and γ, but not P0(e) and D(e). We further assume that the observed compensation contracts
reflect the optimal action taken by that CEO, thus UPPS can be inferred from the observed
contract data. In addition to this “optimal effort” condition, the model assumes that the
observed pay structure (i.e., the allocation of executive compensation in the form of salary, stock
and options) has already attained the level at the lowest cost to the firm. The degree of risk-
aversion (Gamma or γ) can be implied by numerically solving the following optimization
problem. The level of risk-aversion (γ) at which the principal (shareholders) minimizes the cost
of executive compensation subject to incentive compatibility of the agent’s choice of effort (IC)
and participation constraint (IR) that the agent’s expected net utility from the contract is at least
as great as his outside option.
1 0 2 0Min P C
s.t. 1 2 1, 2,( ( , , )) ( ( , , ))T T observed observed observedUPPS W UPPS W (IC)
1 2 1, 2,[ ( ( , , ))] [ ( ( , , ))]T T observed observed observedE U W E U W (IR)
observed , 1 1,observed , 2 2,observed
P0 is the stock price at time 0, and C0 is the call options price estimated by the Black-Scholes
formula.
11
The object function is linear; however there is a non-linear constraint, namely the UPPS
function. We use the estimation method in Dong (2014) to solve this non-linear programming
problem. Basically, the solver applies a sequential quadratic programming (SQP) method which
solves a quadratic programming (QP) sub-problem at each iteration, then updates an estimate
of the Hessian of the Lagrangian at each iteration using the BFGS formula. Internally, the solver
performs a line search using a merit function and the QP sub-problem is solved using the
active-set strategy. There is an additional constraint for the optimization that the value of
gamma is within the range of 0 to 10. This restriction is based on the findings in prior studies
that the degree of risk-aversion is generally smaller than 10 (Arrow 1971; Friend and Blume
1975; Hansen and Singleton 1982, 1984; Epstein and Zin 1991; Ferson and Constantinides 1991;
Jorion and Giovannini 1993; Normandin and St-Amour 1998; Ait-Sahalia and Lo 2000; Guo and
Whitelaw 2006). Unfortunately, when this constraint is strictly enforced as in the first half of the
tests in this paper, many firm-CEO pairs may not have feasible solutions. Because we suspect
that this restriction is too strong to be of much use, we will relax it to be within the range of 0 to
20 in the second half of the tests that relate bank CEO risk-taking to systemic risk.
After obtaining the implied risk-aversion (Gamma or γ) of individual CEOs, we conduct
pooled OLS regression in the following form to study the cross-sectional variation of
managerial risk preference in terms of CEO characteristics (e.g., age, non-firm wealth),
compensation contract characteristics (e.g., salary, stock grants, option grants, stock ownership
and option ownership) and firm financial characteristics (e.g., asset size, financial leverage,
market to book, asset turnover, return on equity, stock return, cash liquidity):
, 0 1 , 2 , 3 , ,i t i t i t i t i tGamma CEO Chars Compensation Chars FirmChars
In order to capture systemic risk in the financial sector we use two econometric
measures: ∆CoVaR (Adrian and Brunnermeier 2016) and SES (Acharya et al. 2016). ∆CoVaR is
the value at risk of the entire financial system conditional on an individual institution in distress.
More formally, ∆CoVaR is the difference between the CoVaR, conditional on a financial
institution being in distress, and the CoVaR, conditional on its operating in its median state. A
number of papers have used the ∆CoVaR measure in various contexts. Brunnermeier, Dong, and
Palia (2012) find that banks actively engaged in trading, investment banking and venture capital
contributed more to systemic risk and Gauthier, Lehar and Souissi (2012) use it to examine
Canadian institutions. Adrian and Brunnermeier (2008) suggest that prudential capital
12
regulation should not just be based on the Value-at-Risk (VaR) of a bank but also on the ∆CoVaR,
which by their predictive power alert regulators who can use them as a basis for a preemptive
countercyclical capital regulation such as a capital surcharge or Pigovian tax.6
Let |system iqCoVaR denote the Value at Risk of the entire financial system (portfolio)
conditional on bank i being in distress (in other words, the loss of bank i is at its level of iqVaR ).
That is, |system iqCoVaR is essentially a measure of systemic risk in the q% quantile of this
conditional probability distribution:
|( | )system system i i iq qProbability R CoVaR R VaR q
Similarly, let | ,system i medianqCoVaR denote the financial system’s VaR, conditional on a bank
operating in its median state (in other words, the return of bank i is at its median level). That is,
| ,system i medianqCoVaR measures the systemic risk when business is normal for bank i :
| ,( | )system system i median i iqProbability R CoVaR R median q
Bank i ’s contribution to systemic risk can be defined as the difference between the
financial system’s VaR conditional on bank i in distress ( |system iqCoVaR ), and the financial
system’s VaR conditional on bank i functioning in its median state ( | ,system i medianqCoVaR ):
| | ,i system i system i medianq q qCoVaR CoVaR CoVaR
To estimate this measure of an individual bank’s systemic risk contribution, i.e., iqCoVaR , we
need to calculate two conditional VaRs for each bank, namely |system iqCoVaR and
| ,system i medianqCoVaR . For the systemic risk conditional on a bank being in distress ( |system i
qCoVaR ),
we run a 1% quantile regression using the weekly data 7 to estimate the coefficients i , i ,
|system i , |system i and |system i :
1i i i it tR Z
6 For detailed discussions of financial institution risk, see Dong and Calluzzo (2015). 7 It should be noted that for each financial institution on average there are three observations for the dependent variable that are in the 1% quantile region given that we have six years of weekly data: 52×6×0.01=3.12. Similarly, we have this data scarcity issue in estimating 0.1% VAR. This problem of data scarcity occurs when the sample size is not very large and the estimated quantile is low (0.1% and 1%) relative to the size of the data, and the problem is made worse by the presence of control variables and fixed effects. We will address this concern using alternative estimation methods in the robustness check section.
13
| | | |1 1
system system i system i system i i system it t tR Z R
and run a 50% quantile (median) regression to estimate the coefficients ,i median and ,i median :
, , ,1
i i median i median i mediant tR Z
where itR is the weekly market-value return of bank i at time t and system
tR is the weekly
market-value return of all N banks ( 1,2,3...,i j N ) in the financial system at time t . 1tZ is
the vector of macroeconomic and finance factors in the previous week, including market return,
equity volatility, liquidity risk, interest rate risk, term structure, default risk and real-estate
return. We obtain value-weighted market returns from the database of the S&P 500 Index CRSP
Indices Daily. We use weekly value-weighted equity returns (excluding ADRs) with all
distributions to proxy for the market return. Volatility is defined as the standard deviation of
log market returns. Liquidity risk is defined as the difference between the three-month LIBOR
rate and the three-month T-bill rate. For the next three interest rate variables we calculate the
changes from this week t to t-1. Interest rate risk is defined as the change in the three-month T-
bill rate. Term structure is defined as the change in the slope of the yield curve (yield spread
between the 10-year T-bond rate and the three-month T-bill rate. Default risk is defined as the
change in the credit spread between the 10-year BAA corporate bonds and the 10-year T-Bond
rate. All interest rate data is obtained from the U.S. Federal Reserve website and Compustat
Daily Treasury database. Real estate returns are proxied by the Federal Housing Finance
Agency’s FHFA House Price Index for all 50 U.S. states.
We predict an individual bank’s VaR and median equity return using the coefficients ˆ i ,
ˆ i , ,ˆ i median and ,ˆ i median estimated from the quantile regressions:
, 1ˆˆ ˆi i i i
q t t tVaR R Z
, , ,1
ˆˆ ˆi median i i median i mediant t tR R Z
After obtaining the unconditional VaRs of an individual bank i ( ,iq tVaR ) and that bank’s asset
return in its median state ( ,i mediantR ), we predict the systemic risk conditional on bank i being in
distress ( |system iqCoVaR ) using the coefficients |ˆ system i , |ˆ system i , and |ˆ system i estimated from this
quantile regression:
| | | |, 1 ,
ˆˆ ˆ ˆsystem i system system i system i system i iq t t t q tCoVaR R Z VaR
14
Similarly, we can calculate the systemic risk conditional on bank i functioning in its median
state ( | ,system i medianqCoVaR ) as:
| , | | | ,, 1
ˆˆ ˆsystem i median system i system i system i i medianq t t tCoVaR Z R
Bank i ’s contribution to systemic risk is the difference between the financial system’s VaR if
bank i is at risk and the financial system’s VaR if bank i is in its median state:
| | ,, , ,i system i system i medianq t q t q tCoVaR CoVaR CoVaR
We are interested in the VaR at the 1% confident level, therefore the systemic risk of individual
bank at q=1% can be written as:
| | ,1%, 1%, 1%,i system i system i mediant t tCoVaR CoVaR CoVaR
And according to Adrian and Brunnermeier (2008), this can be simplified to:
| ,1%, 1%,
ˆ ( )i system i i i mediant t tCoVaR VaR R
We obtain the estimates of VaR0.1% and ∆CoVaR1% of all individual financial institution
for each year from 2005 to 2011 in this first-stage of estimation. Then, in the second-stage, we
pool all VaRs and ∆CoVaRs together and estimate a set of panel regression models consisting of
the estimated financial institution risks (VaR0.1% and ∆CoVaR1%) of the current period (year) and
other firm characteristic variables (market value, financial leverage, log total assets, maturity
mismatch, market-to-book, equity return, equity volatility, and VaR) of the previous time period
(year).
In an attempt to quantify a bank’s vulnerability to financial system failures, Acharya, et
al. (2016) propose a model-implied measure of Systemic Expected Shortfall (SES) that captures
the amount a bank will be undercapitalized by in a systemic event in which the entire financial
system is undercapitalized. Instead of focusing on the return distribution of the banking system
conditional on the distress of a particular bank as measured by ∆CoVaR, the measure of SES
focuses on a bank’s return distribution given that the entire financial system is in distress.
Adrian and Brunnermeier (2008) refer to this form of conditioning as “exposure CoVaR”, as it
measures which financial institution is more exposed to a systemic crisis rather than which
institution contributes more risk to a systemic crisis. In this paper, we estimate a bank’s SES at
the 5% risk level using daily equity returns. The systemic crisis event is the 5% worst days for
the aggregate equity return of the entire banking system in any given year, and the average
15
equity return of a bank during these “worst” market days is defined as this bank’s SES at the 5%
level.
After obtaining both the implied risk-aversion (Gamma or γ) of individual CEOs and the
measures of systemic risk (∆CoVaR and SES) of individual bank holding companies, we conduct
pooled OLS regression in the following form to study the cross-sectional variation of
managerial risk preference in terms of CEO characteristics (e.g., age, non-firm wealth),
compensation contract characteristics (e.g., salary, stock grants, option grants, stock ownership
and option ownership) and firm financial characteristics (e.g., asset size, financial leverage,
market to book, liquidity, loan portfolio, etc.):
, 0 1 , 2 , 3 , ,i t i t i t i t i tSystemic Risk CEO Chars Compensation Chars FirmChars
In addition, to mitigate the omitted variable problem (i.e., unobserved CEO and firm
characteristics), we include firm fixed-effects to exploit the variation over time in our measures
of CEO risk-aversion as reflected by the risk-taking incentives embedded in the executive
compensation contract.
IV. Sample Data
The sample consists of 290 CEOs from the Compustat Executive Compensation database during
the period of 2003 to 2013. This rather small sample size reflects the requirement that these
executives have been serving as CEOs for ten years, meaning their compensation contract
information must exist in the Executive Compensation database for at least ten consecutive
years. The wealth of a CEO is calculated by taking the present value of their 10-year cash pays
including salaries and bonuses plus a 15-year annuity equal to 60% of CEO’s cash compensation.
This estimation is based on the method used by Armstrong, Larcker and Su (2007). The values
of stock price and return, dividend yield, common shares outstanding are taken from the CRSP
database, firm level financial accounting information is from the Compustat Annual database,
and the annual risk-free rate is downloaded from the U.S. Treasury web site. Table 1 shows the
detailed definition of all variables used in this research.
[Insert Table 1 Here]
We require sample data have non-zero values of salary, stock and option holdings,
shares outstanding, stock price, Black-Scholes value, volatility, and total compensation in each
16
year. Table 2 shows the number of observations, mean, standard deviation, maximum and
minimum values of each variable.
[Insert Table 2 Here]
The average CEO in the sample is 58 years old with $40 million wealth as a result of
accumulating his cash compensation during the previous ten years of employment. The average
degree of risk aversion implied by the numerical method proposed in this paper is 4.6, and its
distribution (probability density) and industry means of this Arrow-Pratt measure of relative
risk-aversion are shown in Figure 2. The majority of CEOs, more than half of the sample, are
clustered at a lower level of risk-aversion with mean below 4.0 and the others are clustered at a
higher level of risk-aversion between 7.0 and 9.0. It is interesting to note that chief executives in
wholesale trade industry (5.5) are, on the average, the most risk-averse of all nine industry
groups, followed by those in manufacture and mining industries. CEOs in finance, insurance
and real estate industries (4.9) rank fourth behind those in retail trade, construction, and
agriculture industries in terms of risk-taking.
[Insert Figure 2 Here]
It is important to note that the value of Gamma is within the range of 0 to 10 due to a constraint
that is enforced in the optimization estimation. This restriction is based on the findings in prior
studies that the degree of risk-aversion is generally smaller than 10, and we will relax this
restriction in the later section. We also plot the relations between the degree of risk-aversion and
CEO wealth, age and firm size in Figure 3, 4, and 5 respectively. Besides the fact that risk-
aversions are centered at two different levels similar to what is shown in Figure 1, these graphs
do not suggest a strong association between CEO risk-aversion and personal and firm
characteristics.
[Insert Figure 3, 4 and 5 Here]
An examination of the Pearson’s correlation matrix in Table 3 indicates that correlations
between independent variables are generally small. This low correlation among the covariates
helps prevent the problem of multicollinearity that causes high standard errors and low
significance levels when both variables are included in the same regression. However, there is
three pairs of variables having correlations above or close to 0.9: Stock Grants and Option Grants
(0.91), Stock Grants and Stock Ownership (0.86), and Option Grants and Stock Ownership (0.89). To
17
be cautious, in the following cross-sectional analysis of the determinants of managerial risk
preferences, we will calculate and report the variance inflation factor (VIF) to assess the severity
of multicollinearity in each specification.
[Insert Table 3 Here]
V. Empirical Results
Risk-aversion of CEOs in All Firms
The results from the pooled OLS regressions reported in Table 4 suggest that the implied
managerial risk-aversion is negatively related to the CEO’s non-firm wealth and his stock
option’s moneyness. However, other personal and compensation characteristics, such as CEO
age, wage, current year stock and option grants, and accumulated equity ownership of the firm,
and firm financial characteristic, such as size (Total Assts), profitability (ROE), leverage (Book
Assets to Equity), current asset liquidity (Cash Holding), stock performance (annual return) and
operating efficiency (Asset Turnover) seem unrelated to the degree of risk-aversion.
[Insert Table 4 Here]
The Variance Inflation Factor (VIF) reported in the table is calculated for each
independent variable to determine if these variables display collinearity amongst themselves.
The mean VIFs (ranging from 2.5 to 4.1) reported at the bottom of table are below the cut-off
point of ten (Myers 2000), suggesting no problem with multicollinearity in our regressions.
Based on the significance of coefficient loadings in specifications (1), (2) and (3) we can identify
three factors affecting the degree of relative risk-aversion (Gamma or γ) in a statistically
significant way: CEO Non-firm Wealth (at 1% and 5% level), In-The-Money of Owned Options (i.e.,
the call option’s moneyness, at 1% and 5% level), and the firm’s Financial Leverage (at 10% level).
A useful way to look at the economic significance of the ability of these determinant factors to
affect managerial risk preference is to examine the percentage change in risk-aversion level
when the value of one of these variables is increased by one standard deviation. We estimate
the magnitude of the economic effects for three specifications and report them in Table 5.
[Insert Table 5 Here]
The predicted percentage change in relative risk-aversion (Gamma or γ) that our
regression models generate in response to one standard deviation shock to the CEO’s non-firm
18
wealth is -5.1%, -3.9%, and -4.0% for regression specifications (1), (2), and (3) respectively.
Similarly, the changes in managerial risk-aversion are -3.5% and -8.7% in response to one
standard deviation change in the CEO’s option portfolio moneyness and the firm’s financial
leverage. These results are robust to perturbation of study variates and methods in estimating
the degree of risk aversion by calculating CEO wealth using 5-year income data and by adding
[-10%,+10%] random disturbance to the values of individual wealth, wage, stock grants, option
grants, stock ownership, option ownership, and in-the-money of options. We create a new
sample by requiring CEO compensation contract information exist in the Executive
Compensation database for at least five consecutive years rather than ten consecutive years as
in the previous results.
[Insert Table 6 Here]
The summary statistics in Table 6 show that not only the sample size is larger but also
the estimated level of risk aversion (5.1) is slightly higher than the one obtained in the previous
results (4.6). We repeat our pooled regression analysis using this new data set and the
coefficient estimates are reported in Table 7. In addition to the negative effects of CEO wealth
and option in-the-money, a CEO’s risk-aversion is positively related to her stock grants and the
firm’s financial leverage and negatively related to her option ownership and the firm’s size
(total assets), market-to-book, and asset turnover.
[Insert Table 7 Here]
In the next robustness check, we add [-10%,+10%] random disturbance to the values of
individual wealth, wage, stock grants, option grants, stock ownership, option ownership, and
in-the-money of options and re-estimate the degree of CEO risk-aversion. The summary
statistics in Table 8 and regression results in Table 9 are similar to the ones obtained in the
previous robustness test.
[Insert Table 8 and Table 9 Here]
Risk-aversion of Bank CEOs and Systemic Risk
To understand the relationship between the degree of risk-taking of a bank CEO and the
amount of contagion risk that the bank contributes to the entire financial system, we regress the
19
level of systemic risk on the measure of CEO’s risk-aversion along with other control variables.
Table 10 shows the summary statistics of this rather small sample that only includes CEOs of
bank holding companies.
[Insert Table 10 Here]
Still, the sample size (N=561) is larger than that of the first sample (N=290) in Table 2. The
reason is due to two relaxed constraints in sample construction and numerical estimation. The
first one is the elimination of 10-year tenure requirement in the same firm. Instead, we use the
future value of 10-year annuity payment formula to calculate the initial non-firm wealth of the
CEO where r is the average annual interest rate, CF is approximated by the total compensation
in dollars in including salary, bonus and, restricted stock and stock options :
10(1 ) 1r
Ordinary Annuity rFV CF
The second relaxed constraint is the requirement that the value of Gamma is within the range of
0 to 10. Unfortunately, when this constraint is strictly enforced as shown in the first half of the
tests in this paper, many firm-CEO pairs may not have feasible solutions. Because we suspect
that this restriction is too strong to be of much use, we will relax it to be within the range of 0 to
20 in risk-aversion estimation.
The average CEO age (58 year-old) and initial non-firm wealth ($40 million) in this bank
CEO sample are similar to those in the previous two samples. The average implied-risk
aversion is 15 and this is larger than that of previous findings is due to the relaxed restriction on
the range of Gamma (0 to 20). The first two cross-sectional muntivariate tests are based on
pooled OLS regression with year fixed-effects. The specifications in Table 11 have ∆CoVaR as
the measure of a bank’s systemic risk on the LHS and the Gamma, the degree of risk-aversion of
bank CEOs, on the RHS. The finding is somewhat surprising: after controlling for CEO and
bank characteristics (e.g., age, wealth, wage, stock grants, option grants, stock ownership,
option ownership, option moneyness, the natural logarithm of total assets, financial leverage,
market to book, liquidity, return on asset, annual stock return, loan portfolios, and loan
commitment), the risk-taking incentives embedded in the compensation contract of a bank CEO
is not related to the amount of contagion risk that this bank contributes to the banking system,
Although the signs of Risk-Aversion are negative, they not statistically significant in all
regression specifications.
20
[Insert Table 11 Here]
The regressions in Table 12 use SES as the measure of a bank’s systemic risk, proxying
for the vulnerability of a bank to the financial stability of the entire banking system, on the LHS
and the Gamma, the degree of risk-aversion of bank CEOs, on the RHS. Again, there is no
statistical association between these two variables, suggesting that a risk-taking CEO of a bank
holding company is not necessarily make the bank vulnerable to contagion risk.
[Insert Table 12 Here]
While the evidence presented thus far is convincing, it is still possible that the omitted variable
problem (i.e., unobserved CEO and firm characteristics) may have biased the coefficient
estimates. In the following two tests we include firm fixed-effects, in addition to year fixed-
effects in the previous regression specifications, to exploit the variation over time in our
measures of bank CEO risk-aversion as reflected by the risk-taking incentives embedded in the
executive compensation contract. The basic specifications in Table 13 and Table 14 are same as
the ones in Table 11 and Table 12 respectively, except including the bank fixed-effects. The
insignificant coefficient estimates of Risk-Aversion remain in both tables, suggesting that even
the risk-taking incentives increase in the compensation contract, they do not necessarily increase
the contagion risk of the bank.
[Insert Table 13 and Table 14 Here]
Finally, it is noted in Dittmann and Maug (2007) that the calibration of a principal-agent
model using observed data is sensitive to the CEO’s non-firm wealth, which is often not
observable, and each of the two estimation methods of CEO wealth presented in this research
has its limitations. In the first method, the requirement of 10-year or 5-year continuous
compensation data of a CEO in the Execcomp dataset reduces the sample size. It is often the
case that some of them left the sample and then reappeared in a later year. In the second
method, whereas the use of 10-year annuity payment formula based on one-year income data
(cash flow in the initial year) helps increase the sample size, it has to assume that future incomes
do not fluctuate over time. Therefore, as a robustness check, we combine both estimation
methods to create a simple two-stage method to predict CEO wealth. In the first stage, we
conduct a pooled OLS regression on a sample of CEOs with 10-year accumulated wealth (from
21
the first method) to estimate the relationship between the 10-year accumulated wealth and the
cash flow in the initial year (used in the second method):
, , , ,i t i t i t t i tWealth Cashflow Age
In the second stage, we use the coefficient estimates (α, β, γ, and λ) and the income cash flow
and CEO age in each year in the larger sample (for the second method) to predict a CEO’s
wealth:
, , , ,ˆ ˆˆ ˆ ˆi t i t i t t i tW CF AGE
After obtaining the fitted wealth, we repeat the regression models in Tables 13 and 14. Overall,
the insignificant coefficient estimates of risk-aversion shown in Tables 15 and 16 confirm our
previous findings that risk-taking preference of bank CEOs is not related to the bank’s systemic
risk measured in both CoVaR and SES.
[Insert Table 15 and Table 16 Here]
VI. Discussion and Conclusion
Fitting a principal-agent model using observed executive compensation data produces a
number of insights that have not been presented in the empirical corporate finance literature.
We find a very low degree of risk-aversion among CEOs with the average Arrow-Pratt measure
of relative risk-aversion (CRRA) being 4.6 for 290 managers who have served as CEOs for more
than ten years. This result is, to some extent, consistent with the theoretical finding in the
previous studies. For example, Hemmer, Kim and Verrecchia (2000) use a principal–agent
model to show that in the case of log utility, if relative risk aversion is less than one, the optimal
contract is convex in stock value. The assumptions behind our numerical estimation method are
“optimal effort” and “optimal pay”. The first one means that when a manager accepts the offer
of employment to become or continue to serve as the CEO of the firm, the compensation
contract reflects the optimal level of efforts that the CEO will and must exert in order to
maximize the firm value. The optimal pay assumption suggests that the observed compensation
contract offered by the firm has already attained the level at the lowest cost to the firm.
To better understand the cross-sectional variation of managerial risk preferences, we
study the determinants of the model-implied risk-aversion by conducting pooled OLS
22
regression and identified two factors that are negatively related to CEO risk-aversion: CEO
wealth and their options portfolio’s moneyness. Other personal and compensation
characteristics, such as CEO age, wage, current year stock and option grants, and accumulated
equity ownership of the firm, and firm financial characteristic, such as size, profitability,
leverage, liquidity and operating efficiency, seem unrelated to CEO risk-aversion.
Perhaps the most striking result from this research is a non-result: the lack of
relationship between bank CEOs’ risk-taking incentives and systemic risk in a very important
financial sector: banking. Executive compensation policy has been controversial within the
corporate finance literature and mainstream media and often blamed for encouraging excessive
risk-taking in financial services that stoked the global economic crisis in 2008-10. Yet, the
evidence presented here does not seem to support the claim that risk-taking incentives
embedded in the executive compensation contracts in U.S. banks are related to contagion risk in
the banking sector.
In sum, we find somewhat mixed evidence in favor of the presence of excessive risk
taking among CEOs in many industries including banking. When interpreting the evidence
presented in this paper, however, it is important to bear in mind that our results rely on the
critical assumption of an efficient managerial labor market. The competitive equilibrium in the
CEO labor market is reflected in the observed CEO compensation contract which indicates the
optimal level of the CEO’s effort and the lowest cost to the firm. If these conditions hold, the
actual managerial pay is an unbiased estimate of the CEO’s expected marginal contribution to
the firm’s outcome. As Kaplan (2008) points out, although far from perfect, CEO pay practices
are mainly driven by market competition. On one hand, if a CEO thinks the pay is too low, he
will not accept the job offer and take another post offering higher pay. On the other hand, a
high paying job creates competition among CEOs, and only the best performer gets the job,
hence exerting maximum effort. Furthermore, it can be argued that in reality the principal-agent
model is not an appropriate model to describe the relationship between the shareholders and
the CEO. Nevertheless, we believe one important contribution of this paper is to provide a
relatively clean framework for evaluating managerial risk preferences embedded in the
observed executive compensation contracts.
23
REFERENCE
Acharya, Viral, Lasse Pedersen, Thomas Philippon, and Mathew Richardson, 2016, Measuring Systemic Risk, Review of Financial Studies, 30, 2–47. Ackerberg, Daniel and Maristella Botticini, 2002, Endogenous Matching and the Empirical Determinants of Contract Form, Journal of Political Economy, 110, 564–591. Adrian, Tobias and Markus Brunnermeier, 2016, CoVaR, American Economic Review, 106, 1705–1741. Ait-Sahalia, Yacine and Andrew Lo, 1998, Nonparametric estimation of state-price densities implicit in financial asset prices, Journal of Finance, 53, 499–547. Ait-Sahalia, Yacine and Andrew Lo, 2000, Non-parametric Risk Management and Implied Risk Aversion, Journal of Econometrics, 94, 9–51. Allen, Douglas and Dean Lueck, 1995, Risk Preferences and the Economics of Contracts, American Economic Review, Papers and Proceedings, 85, 447–451. Armstrong, Christopher, David Larcker and Che-Lin Su, 2007, Working Paper, Stanford University and Northwestern University. Arrow, Kenneth, 1971, Essays in the Theory of Risk Bearing. North Holland, Amsterdam. Aseff, Jorge and Manuel Santos, 2005, Stock Options and Managerial Optimal Contracts, Economic Theory, 26, 813–837. Bebchuk, Lucian, 2009, Regulate financial pay to reduce risk-taking, Opinion, Financial Times, August 3rd. Becker, Bo, 2006, Wealth and Executive Compensation, Journal of Finance, 61, 1, 379–397. Bennett, Rosalind, Levent Guntay and Haluk Unal, 2015, Inside Debt, Bank Default Risk and Performance during the Crisis, Journal of Financial Intermediation, 24, 487–513. Bettis, J. Carr, John Bizjak, and Michael Lemmon, 2005, Exercise behavior, valuation, and the incentive effects of employee stock options, Journal of Financial Economics, 76, 445–470. Bliss, R.R., and N. Panigirtzoglou, 2002, Testing the stability of implied probability density functions, Journal of Banking and Finance, 26, 381–422. Bliss, R.R., and N. Panigirtzoglou, 2004, Option-implied risk aversion estimates, Journal of Finance, 59, 407–446. Borghans, Lex, James Heckman, Bart Golsteyn, and Huub Meijers, 2009, Gender differences in risk aversion and ambiguity aversion, Journal of European Economic Association, 7, 649–658.
24
Brunnermeier, Markus, G. Nathan Dong, and Darius Palia, 2012, Non-interest Income and Systemic Risk, AFA 2012 Chicago Meetings Paper. Cain, Matthew and Stephen McKeon, 2016, CEO Personal Risk-Taking and Corporate Policies, Journal of Financial and Quantitative Analysis, 51, 139–164. Calluzzo, Paul and Gang Nathan Dong, 2015, Has the financial system become safer after the crisis? The changing nature of financial institution risk, Journal of Banking and Finance, 53, 233–248. Campbell, John, Andrew Lo and Craig McKinlay, 1997, The Econometrics of Financial Markets, Princeton University Press. Carpenter, Jennifer, 2000, Does Option Compensation Increase Managerial Risk Appetite, Journal of Finance, 55, 2311–2331. Dittmann, Ingolf and Ernst Maug, 2007, Lower Salaries and No Options? On the Optimal Structure of Executive Pay, Journal of Finance, 62, 303–343. Docking, Diane Scott, Mark Hirschey, and Elaine Jones, 1997, Information and Contagion Effects of Bank Loan-Loss Reserve Announcements, Journal of Financial Economics, 43, 219–239. Dohmen, Thomas, Armin Falk, David Huffmann, and Uwe Sunde, 2010, Are Risk Aversion and Impatience Related to Cognitive Ability?, American Economic Review, 100, 1238–1260. Dong, Gang Nathan, 2014, Excessive financial services CEO pay and financial crisis: Evidence from calibration estimation, Journal of Empirical Finance, 27, 75–96. Epstein, Larry and Stanley Zin, 1991, Substitution, Risk Aversion and the Temporal Behaviour of Consumption and Asset Returns: An Empirical Analysis, Journal of Political Economy, 99, 263–268. Fahlenbrach, Rudiger and Rene Stulz, 2011, Bank CEO Incentives and the Credit Crisis, Journal of Financial Economics, 99, 11–26. Ferson, Wayne and George Constantinides, 1991, Habitat Persistence and Durability in Aggregate Consumption: Empirical Tests, Journal of Financial Econometrics, 29, 199–240. Flannery, Mark J., 1998, Using Market Information in Prudential Bank Supervision: A Review of the U.S. Empirical Evidence, Journal of Money, Credit, and Banking, 30, 273–305. Friend, Irwin and Marshall Blume, 1975, The Demand for Risky Assets, American Economic Review, 65, 900–922. Gauthier, Celine, Alfred Lehar, and Moez Souissi, 2012, Macroprudential Capital Requirements and Systemic Risk, Journal of Financial Intermediation, 21, 594–618.
25
Guo, Hui and Robert Whitelaw, 2006, Uncovering the Risk-Return Relation in the Stock Market, Journal of Finance, 61, 1433–1463. Grahama, John, Campbell Harvey, and Manju Puri, 2013, Managerial attitudes and corporate actions, Journal of Financial Economics, 109, 103–121. Hall, Brian and Kevin Murphy, 2000, Optimal Exercise Prices for Executive Stock Options, American Economic Review, 90, 209–214. Hall, Brian and Kevin Murphy, 2002, Stock Options for Undiversified Executives, Journal of Accounting and Economics, 33, 3–42. Hansen, Lars and Kenneth Singleton, 1982, Generalized Instrumental Variables Estimation of Nonlinear Rational Expectations Models, Econometrica, 50, 1269–1286. Hansen, Lars and Kenneth Singleton, 1984, Errata: Generalized Instrumental Variables Estimation of Nonlinear Rational Expectations Models, Econometrica, 52, 267–268. Hemmer, T., O. Kim, and R.E. Verrecchia, 2000, Introducing convexity into optimal compensation contracts, Journal of Accounting and Economics, 28, 307–327. Holmstrom, Bengt, 1979, Moral Hazard and Observability, Bell Journal of Economics, 10, 74–91. Ingersoll, Jonathan, 1998, Approximating American options and other financial contracts using barrier derivatives, Journal of Computational Finance, 2, 85–112. International Accounting Standards Board, 2004, Share-Based Payment. International Financial Reporting Standards 2. Jensen, Michael and William Meckling, 1976, Theory of the Firm: Managerial Behavior, Agency Costs, and Ownership Structure, Journal of Financial Economics, 3, 305–360. Jorion, Philippe and Alberto Giovannini, 1993, Time Series Test of a Non-Expected Utility Model of Asset Pricing, European Economic Review, 37, 1083–1100. Kadan and Swinkels, Forthcoming, Stock or Options? Moral Hazard, Firm Viability, and the Design of Compensation Contracts, 2008, Review of Financial Studies, 21, 451–482. Kang, B.J., T.S. Kim, 2006, Option implied risk preferences: an extension to wider classes of utility functions, Journal of Financial Markets, 9, 180–198. Kaplan, Steven, 2008, Are U.S. CEOs Overpaid?, Academy of Management Perspectives, 22, 5–20. Kaufman, George, 1994, Bank Contagion: A Review of the Theory and Evidence. Journal of Financial Services Research, 8, 123–150.
26
Lambert, Richard, David Larcker and Robert Verrecchia, 1991, Portfolio Considerations in Valuing Executive Compensation, Journal of Accounting Research, 29, 129-149. Lewellen, K., 2006, Financing decisions when managers are risk averse, Journal of Financial Economics 82, 551–589. MacCrimmon, Kenneth and Donald Wehrung, 1990, Characteristics of Risk Taking Executives, Management Science, 36, 422–435. Mann, H. B., and D.R. Whitney, 1947, On a Test of Whether One of Two Random Variables is Stochastically Larger Than the Other, Annals of Mathematical Statistics, 18, 50–60. Mehran, Hamid, 1995, Executive Compensation Structure, Ownership, and Firm Performance, Journal of Financial Economics, 38, 163–184. Meulbroek, Lisa, 2001, The Efficiency of Equity-linked Compensation: Understanding the Full Cost of Awarding Executive Stock Options, Financial Management, 30, 5–30. Murphy, Kevin, 1999, Executive compensation, Handbook of Labor Economics 3, 2485–2563, North Holland, Amsterdam. Murphy, Kevin, 2013, Regulating Banking Bonuses in the European Union: a Case Study in Unintended Consequences, European Financial Management, 19, 631–657. Myers, Raymons, 2000, Classical and Modern Regression with Applications, Duxbury Press, Boston, MA. Normandin, Michel and Pascal St-Amour, 1998, Substitution, Risk Aversion, Taste Shocks and Equity Premia, Journal of Applied Econometrics, 13, 265–281. Rivlin, Alice, 2009, Reducing Systemic Risk in the Financial Sector, Testimony before the Housing Committee on Financial Services, July 21st. Ross, Stephen, 2004, Compensation, Incentives, and the Duality of Risk Aversion and Riskiness, Journal of Finance, 59, 207-225. Santomero, Anthony and Jeffrey Trester, 1998, Financial innovation and bank risk taking, Journal of Economic Behavior & Organization, 35, 25–37. Securities and Exchange Commission, 2005, Staff Accounting Bulletin No. 107. Securities and Exchange Commission, 2015, Pay Ratio Disclosure, 17 CFR Parts 229 and 249. Shaw, Kathryn, 1996, An Empirical Analysis of Risk Aversion and Income Growth, Journal of Labor Economics, 14, 626–653.
27
Skaperdas, Stergios and Gan Li, 1995, Risk Aversion in Contests, Economic Journal, 105, 951–962. Wilcoxon, F., 1945, Individual Comparisons by Ranking Methods, Biometrics Bulletin, 1, 80–83.
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Figure 1. CEO risk-aversion over time
Mean value 0
12
34
56
Gam
ma
1997
1998
1999
2000
2001
2002
2003
2004
2005
2006
2007
2008
2009
2010
2011
2012
2013
Upper adjacent value, 75th percentile, median, 25th percentile, and lower adjacent value
23
45
67
89
10G
amm
a
1997
1998
1999
2000
2001
2002
2003
2004
2005
2006
2007
2008
2009
2010
2011
2012
2013
excludes outside values
29
Figure 2. Distribution of CEO risk-aversion
Density of risk-aversion measured in Gamma 0
.2.4
.6.8
De
nsity
2 4 6 8 10Gamma
Industry mean of CEO risk-aversion
4.2
5.1
4.5
5.25
5.5
4.64.9
5
01
23
45
6G
amm
a
Agricu
lture
, For
estry
Mini
ng
Constr
uctio
n
Man
ufac
turin
g
Trans
porta
tion,
Com
mun
icatio
ns, U
tilitie
s
Who
lesa
le T
rade
Retail
Tra
de
Finan
ce, I
nsur
ance
, Rea
l Esta
te
Servic
es
32
Figure 5. CEO risk-aversion and firm size
24
68
10G
amm
a
6 8 10 12 14Natural Logarithm of Total Assets
33
Table 1. Variable definitions Variable Name Definition
Risk Aversion
Gamma (γ) Risk aversion measure
CEO Characteristics
Age Age in years
Wealth ($ thousand) Total wealth ÷ 1,000
Compensation Characteristics log(Total assets)
Wage ($ thousand) Current year cash-based salary ÷ 1,000
Stock Grants (Current year granted stocks ÷ Total shares outstanding) × 100
Option Grants (Current year granted options ÷ Total shares outstanding) × 100
Stock Ownership to Total Shares Outstanding (%) (All granted stocks ÷ Total shares outstanding) × 100
Option Ownership to Total Shares Outstanding (%) (All granted options ÷ Total shares outstanding) × 100
In-The-Money of Owned Options Stock Price – Average strike of all granted options
Firm Characteristics
Natural Logarithm of Total Assets log(Total assets)
Financial Leverage Total assets ÷ Book equity
Market to Book Stock market value ÷ Book equity
Asset Turnover Revenue ÷ Total assets
Return on Equity Net income ÷ Book equity
Annual Stock Return Accumulated stock return during the year
Cash Holding to Total Assets (Cash + Cash equivalents) ÷ Total assets
34
Table 2. Summary statistics
The value of risk-aversion is estimated with a range restriction [0, 10].
Variable N Mean Standard Deviation
Minimum Maximum
Risk Aversion
Gamma (γ) 290 4.613 1.836 2.820 9.795
CEO Characteristics
Age 290 57.74 4.754 45 74
Wealth 290 40.47 35.74 4.921 222.0
Compensation Characteristics
Wage 290 1.663 1.460 0.3079 8.803
Stock Grants 290 0.0434 0.1288 0.0004 2.096
Option Grants 290 0.1682 0.4921 0.0063 8.162
Stock Ownership to Total Shares Outstanding (%) 290 0.8832 3.345 0.0037 52.15
Option Ownership to Total Shares Outstanding (%) 290 1.224 1.313 0.0156 14.28
In-The-Money of Owned Options 290 16.61 15.83 0 120.4
Firm Characteristics
Natural Logarithm of Total Assets 290 8.801 1.358 5.505 13.53
Financial Leverage 290 3.587 3.203 1.159 24.01
Market to Book 290 3.740 3.018 0.4543 24.08
Asset Turnover 290 0.9051 0.6385 0.0386 3.681
Return on Equity 290 0.1653 0.3331 -4.691 1.084
Annual Stock Return 290 0.1733 0.3137 -0.6784 2.559
Cash Holding to Total Assets 290 0.1108 0.1147 0.0005 0.8051
35
Table 3. Correlation matrix
The lower-left triangle is the Pearson's correlation matrix and t-statistics are shown in the parentheses with ***, ** and * indicating its statistical significant level of 1%, 5% and 10% respectively.
Ris
k-av
ersi
on
(Gam
ma
or γ
)
Age
Wea
lth
Wag
e
Stoc
k G
rant
s
Op
tion
Gra
nts
Stoc
k O
wne
rshi
p
Op
tion
Ow
ners
hip
In-T
he-M
oney
Log
Tot
al A
sset
s
Fina
ncia
l Lev
erag
e
Mar
ket t
o B
ook
Ass
ets
Tur
nove
r
Ret
urn
on E
quit
y
Ann
ual S
tock
R
etu
rn
Age -0.0895
Wealth -0.188*** 0.161***
Wage -0.133** 0.165*** 0.332***
Stock Grants 0.007 -0.022 -0.006 0.170***
Option Grants 0.001 0.059 0.019 0.198*** 0.914***
Stock Ownership -0.079 0.126** 0.0607 0.242*** 0.859*** 0.887***
Option Ownership -0.056 0.102* 0.018 0.107* 0.622*** 0.735*** 0.673***
In-The-Money -0.066 -0.019 0.130** 0.109* -0.090 -0.064 -0.017 -0.055
Log Total Assets -0.171*** 0.078 0.295*** 0.360*** -0.204*** -0.210*** -0.147** -0.442*** 0.065
Financial Leverage -0.067 0.020 0.044 0.171*** -0.018 -0.052 -0.011 -0.102* -0.086 0.437***
Market to Book -0.086 -0.007 0.438*** -0.009 -0.089 -0.087 -0.073 -0.044 0.284*** -0.074 0.176***
Asset Turnover 0.051 -0.013 -0.003 -0.087 -0.039 -0.036 -0.026 0.033 0.102* -0.292*** -0.418*** 0.152***
Return on Equity -0.0282 0.121** 0.273*** 0.0814 -0.0846 -0.0368 -0.0464 -0.0835 0.186*** 0.180*** -0.141** -0.0656 0.189***
Annual Stock Return -0.009 -0.079 -0.084 -0.058 0.046 0.010 0.021 -0.011 0.205*** -0.179*** -0.083 0.118** 0.024 -0.011
Cash Holding 0.031 -0.098* 0.109* -0.062 0.267*** 0.231*** 0.200*** 0.189*** -0.018 -0.303*** -0.067 0.261*** -0.171*** -0.414*** 0.136**
36
Table 4. Pooled regression analysis of the determinants of implied managerial risk-aversion
The dependent variable is the model-implied level of managerial risk-aversion. The independent variables include CEO age, non-firm wealth, wage, stock grants, option grants, stock ownership, option ownership, option moneyness, the natural logarithm of total assets, financial leverage, market to book, total asset turnover, return on equity, annual stock return, and cash holding. All specifications include year and industry fixed-effects with clustered standard errors on the industry level. t-statistics are shown in the parentheses with ***, ** and * indicating its statistical significant level of 1%, 5% and 10% respectively. Dependent Variable: Risk Aversion (Gamma) (1) (2) (3)
CEO Characteristics
Age -0.0113 (-0.53)
-0.0138 (-0.70)
-0.00500 (-0.28)
Wealth -0.00655***
(-3.23) -0.00509**
(-2.52) -0.00521**
(-2.04)
Compensation Characteristics
Wage
0.0677 (1.44)
0.0666 (0.95)
Stock Grants
1.273 (0.59)
1.356 (0.63)
Option Grants
0.565 (1.25)
0.544 (1.14)
Stock Ownership to Total Shares Outstanding (%)
-0.135 (-1.13)
-0.116 (-0.95)
Option Ownership to Total Shares Outstanding (%)
-0.0489 (-0.40)
-0.150 (-0.97)
In-The-Money of Owned Options
-0.00903*** (-2.80)
-0.0101** (-2.72)
Firm Characteristics
Natural Logarithm of Total Assets
-0.158 (-1.41)
Financial Leverage
-0.125* (-1.88)
Market to Book
0.0453 (1.11)
Asset Turnover
-0.143 (-0.50)
Return on Equity
-0.0959 (-0.66)
Annual Stock Return
-0.300 (-0.76)
Cash Holding to Total Assets
0.229 (0.25)
Constant 4.743*** (3.77)
5.040*** (4.36)
6.323*** (4.31)
Year Fixed-Effects Yes Yes Yes
Industry Fixed-Effects Yes Yes Yes
Standard Errors Clustered on Industry Level Yes Yes Yes
N 290 290 290
Adj. R-squared 0.070 0.070 0.072
Mean VIF 2.52 3.44 4.07
37
Table 5. Economic significance
The following table estimates the predicted percentage change in relative risk-aversion (Gamma or γ) that our models generate in response to one standard deviation shocks to three significant explanatory variables of interest: CEO non-firm wealth, moneyness of owned options, and firm financial leverage.
Regression Model Specification (1) (2) (3)
Determinant Factor
CEO Non-firm Wealth -5.1% -3.9% -4.0%
In-The-Money of Owned Options (Call Option Moneyness)
-3.1% -3.5%
Financial Leverage -8.7%
38
Table 6. Summary statistics of robustness checks with 5-year wealth
This sample requires CEO compensation contract information exist in the Executive Compensation database for at least five consecutive years rather than ten consecutive years. The value of risk-aversion is estimated with a range restriction [0, 10].
Variable N Mean Standard Deviation
Minimum Maximum
Risk Aversion
Gamma (γ) 1,566 5.089 1.878 0.5262 9.881
CEO Characteristics
Age 1,566 56.58 5.259 40 74
Wealth 1,566 20.41 30.13 0.1652 760.1
Compensation Characteristics
Wage 1,566 1.850 2.216 -0.4437 23.47
Stock Grants 1,566 0.05026 0.1166 -0.003851 3.073
Option Grants 1,566 0.1657 0.2944 0 8.162
Stock Ownership to Total Shares Outstanding (%) 1,566 1.021 3.406 0 52.15
Option Ownership to Total Shares Outstanding (%) 1,566 1.156 1.128 0.01392 14.28
In-The-Money of Owned Options 1,566 17.24 15.50 0 162.9
Firm Characteristics
Natural Logarithm of Total Assets 1,566 8.667 1.578 4.529 14.19
Financial Leverage 1,566 3.886 7.265 1.09965 173.4953
Market to Book 1,566 4.17695 22.09 0.02944 831.0
Asset Turnover 1,566 0.9328 0.7497 0.02769 5.400
Return on Equity 1,566 0.2113 1.452 -4.690 55.49
Annual Stock Return 1,566 0.1798 0.3286 -0.7966 2.840
Cash Holding to Total Assets 1,566 0.1036 0.1139 0 0.8611
39
Table 7. Robustness checks with 5-year wealth
This sample requires CEO compensation contract information exist in the Executive Compensation database for at least five consecutive years rather than ten consecutive years. The dependent variable is the model-implied level of managerial risk-aversion. The independent variables include CEO age, non-firm wealth, wage, stock grants, option grants, stock ownership, option ownership, option moneyness, the natural logarithm of total assets, financial leverage, market to book, total asset turnover, return on equity, annual stock return, and cash holding. All specifications include year and industry fixed-effects with clustered standard errors on the industry level. t-statistics are shown in the parentheses with ***, ** and * indicating its statistical significant level of 1%, 5% and 10% respectively. Dependent Variable: Risk Aversion (Gamma)
CEO Characteristics
Age -0.00950 (-0.80)
Wealth -0.00526**
(-2.52)
Compensation Characteristics
Wage 0.00659 (0.21)
Stock Grants -2.889*** (-3.97)
Option Grants 1.447*** (4.27)
Stock Ownership to Total Shares Outstanding (%) -0.0402* (-1.79)
Option Ownership to Total Shares Outstanding (%) -0.332*** (-4.87)
In-The-Money of Owned Options -0.0185***
(-4.28)
Firm Characteristics
Natural Logarithm of Total Assets -0.530*** (-7.62)
Financial Leverage 0.0653***
(3.45)
Market to Book -0.0416***
(-3.26)
Asset Turnover -0.346** (-2.33)
Return on Equity 0.334* (1.81)
Annual Stock Return -0.0426 (-0.28)
Cash Holding to Total Assets -0.414 (-0.94)
Constant 9.998*** (9.81)
Year Fixed-Effects Yes
Industry Fixed-Effects Yes
Standard Errors Clustered on Industry Level Yes
N 1,566
Adj. R-squared 0.186
Mean VIF 8.64
40
Table 8. Summary statistics of robustness checks with 5-year wealth and random disturbance
This sample requires CEO compensation contract information exist in the Executive Compensation database for at least five consecutive years rather than ten consecutive years and adds [-10%,10%] random disturbance to the values of wealth, wage, stock grants, option grants, stock ownership, option ownership, and in-the-money of options for estimating risk-aversion (gamma). The value of risk-aversion is estimated with a range restriction [0, 10].
Variable N Mean Standard Deviation
Minimum Maximum
Risk Aversion
Gamma (γ) 1,661 5.068 1.465 0.1841 9.543
CEO Characteristics
Age 1,566 56.52 5.306 40 74
Wealth 1,566 20.38 30.27 0.07573 760.1
Compensation Characteristics
Wage 1,566 1.867 2.275 -0.4437 23.47
Stock Grants 1,566 0.04997 0.1172 -0.004217 3.073
Option Grants 1,566 0.1699 0.3089 0 8.162
Stock Ownership to Total Shares Outstanding (%) 1,566 1.004 3.333 0 52.15
Option Ownership to Total Shares Outstanding (%) 1,566 1.165 1.131 0.01392 14.28
In-The-Money of Owned Options 1,566 17.01 15.39 0 162.9
Firm Characteristics
Natural Logarithm of Total Assets 1,566 8.638 1.585 4.463 14.19
Financial Leverage 1,566 3.973 7.841 1.099 173.4
Market to Book 1,566 4.196 21.56 0.02944 831.0
Asset Turnover 1,566 0.9326 0.7461 0.02769 5.400
Return on Equity 1,566 0.2057 1.424 -7.402 55.49
Annual Stock Return 1,566 0.1800 0.3276 -0.7966 2.840
Cash Holding to Total Assets 1,566 0.1034 0.1156 0 0.8611
41
Table 9. Robustness checks with 5-year wealth and random disturbance
This sample requires CEO compensation contract information exist in the Executive Compensation database for at least five consecutive years rather than ten consecutive years and adds [-10%,10%] random disturbance to the values of wealth, wage, stock grants, option grants, stock ownership, option ownership, and in-the-money of options for estimating risk-aversion (gamma). The dependent variable is the model-implied level of managerial risk-aversion. The independent variables include CEO age, non-firm wealth, wage, stock grants, option grants, stock ownership, option ownership, option moneyness, the natural logarithm of total assets, financial leverage, market to book, total asset turnover, return on equity, annual stock return, and cash holding. All specifications include year and industry fixed-effects with clustered standard errors on the industry level. t-statistics are shown in the parentheses with ***, ** and * indicating its statistical significant level of 1%, 5% and 10% respectively. Dependent Variable: Risk Aversion (Gamma)
CEO Characteristics
Age -0.00357 (-0.38)
Wealth -0.00541***
(-3.26)
Compensation Characteristics
Wage 0.00310 (0.09)
Stock Grants -1.338** (-2.09)
Option Grants 1.183*** (5.38)
Stock Ownership to Total Shares Outstanding (%) -0.0475***
(-2.83)
Option Ownership to Total Shares Outstanding (%) -0.287*** (-5.02)
In-The-Money of Owned Options -0.0206***
(-6.31)
Firm Characteristics
Natural Logarithm of Total Assets -0.485*** (-8.09)
Financial Leverage 0.0198 (1.11)
Market to Book -0.0255** (-2.29)
Asset Turnover -0.288** (-2.60)
Return on Equity 0.307** (2.64)
Annual Stock Return 0.0161 (0.22)
Cash Holding to Total Assets -0.927** (-2.21)
Constant 10.08*** (14.68)
Year Fixed-Effects Yes
Industry Fixed-Effects Yes
Standard Errors Clustered on Industry Level Yes
N 1,661
Adj. R-squared 0.279
Mean VIF 8.25
42
Table 10. Summary statistics of bank holding companies
This sample includes CEO compensation contract information of all bank holding companies. Due to the sample size constraint, the value of risk-aversion is estimated with a range restriction [0, 20].
Variable N Mean Standard Deviation
Minimum Maximum
Risk Aversion
Gamma (γ) 561 14.81 5.309 0.000 19.99
CEO Characteristics
Age 561 56.64 6.045 34 75
Wealth 561 42.32 65.74 1.177 460.4
Compensation Characteristics
Wage 561 2.127 2.546 0.3244 15.34
Stock Grants 561 0.01774 0.02504 0.000 0.1308
Option Grants 561 0.1251 0.1528 0.002217 0.9645
Stock Ownership to Total Shares Outstanding (%) 561 1.468 4.259 0.01697 32.43
Option Ownership to Total Shares Outstanding (%) 561 0.7971 0.9161 0.04272 5.421
In-The-Money of Owned Options 561 12.47 10.76 0.02812 52.71
Firm Characteristics
Natural Logarithm of Total Assets 561 16.95 1.515 14.40 21.00
Financial Leverage 561 6.867 2.705 2.748 17.79
Market to Book 561 2.252 1.052 0.7368 6.082
Liquidity 561 0.2876 0.1348 0.06828 0.9017
Return on Asset 561 0.01218 0.004537 0.001344 0.02926
Annual Stock Return 561 0.1932 0.2670 -0.3248 0.9764
C&I Loans/Total Loans 561 0.2326 0.1428 0.000 0.7159
Real estate Loans/Total Loans 561 0.5324 0.2142 0.000 0.9876
Agriculture Loans/Total Loans 561 0.004506 0.007572 0.000 0.04445
Consumer Loans/Total Loans 561 0.1209 0.1046 0.0000691 0.5442
Non-performing Loans/Total Loans 561 0.009728 0.01141 0.000 0.06796
Loan Commitment 561 0.3148 0.1601 0.05327 0.8172
43
Table 11. Regressions of systemic risk (ΔCoVaR) and bank characteristics This sample includes CEO compensation contract information of all bank holding companies. The dependent variable is systemic risk measured in ΔCoVaR. The independent variables include the model-implied level of managerial risk-aversion with a range restriction of [0, 20], CEO age, non-firm wealth, wage, stock grants, option grants, stock ownership, option ownership, option moneyness, the natural logarithm of total assets, financial leverage, market to book, liquidity, return on asset, annual stock return, loan portfolios, and loan commitment. All specifications include year fixed-effects with clustered standard errors on the year level. t-statistics are shown in the parentheses with ***, ** and * indicating its statistical significant level of 1%, 5% and 10% respectively. Dependent Variable: ΔCoVaR (1) (2) (3) (4) (5) (6)
Risk Aversion -0.00535 (-0.72)
-0.0108 (-1.50)
-0.00634 (-0.86)
-0.0112 (-1.56)
-0.00545 (-0.64)
-0.0101 (-1.24)
Age
-0.0174*** (-3.50)
-0.0195*** (-3.96)
-0.0183*** (-3.68)
-0.0201*** (-4.08)
Wealth
0.00175*** (3.05)
0.00111** (2.02)
0.000988 (1.36)
0.000214 (0.30)
Wage
0.0405* (1.88)
0.0474** (2.48)
Stock Grants
0.752 (0.48)
0.515 (0.32)
Option Grants
0.299 (1.06)
0.349 (1.33)
Stock Ownership to Total Shares
-0.00871 (-1.11)
-0.0127 (-1.52)
Option Ownership to Total Shares
-0.0440 (-0.97)
-0.0647 (-1.42)
In-The-Money of Owned Options
-0.00573 (-1.18)
-0.00162 (-0.35)
Natural Logarithm of Total Assets -0.253*** (-9.30)
-0.183*** (-5.55)
-0.287*** (-9.51)
-0.200*** (-5.54)
-0.308*** (-7.89)
-0.232*** (-5.36)
Financial Leverage 0.0403* (1.71)
0.0120 (0.46)
0.0469** (2.08)
0.0170 (0.67)
0.0519** (2.23)
0.0260 (0.99)
Market to Book -0.154** (-2.53)
-0.130** (-2.14)
-0.157** (-2.55)
-0.140** (-2.28)
-0.143** (-2.22)
-0.140** (-2.16)
Liquidity 0.317 (1.16)
1.068*** (3.45)
0.141 (0.52)
0.881*** (2.82)
0.114 (0.40)
0.806** (2.49)
Return on Asset -7.314 (-0.65)
-13.12 (-1.17)
-7.626 (-0.67)
-11.43 (-1.00)
-5.444 (-0.48)
-8.278 (-0.74)
Annual Stock Return -0.137 (-0.68)
-0.0955 (-0.51)
-0.177 (-0.88)
-0.119 (-0.62)
-0.143 (-0.66)
-0.129 (-0.62)
C&I Loans/Total Loans
-0.533* (-1.89)
-0.664** (-2.39)
-0.760*** (-2.65)
Real estate Loans/Total Loans
0.935*** (3.57)
0.849*** (3.20)
0.759*** (2.72)
Agriculture Loans/Total Loans
10.49** (2.10)
8.582* (1.78)
8.763* (1.80)
Consumer Loans/Total Loans
0.539 (1.33)
0.425 (1.06)
0.341 (0.83)
Non-performing Loans/Total Loans
9.690*** (2.66)
8.606** (2.33)
7.956** (2.09)
Loan Commitment
-0.306 (-0.92)
-0.358 (-1.06)
-0.455 (-1.32)
N 561 561 561 561 561 561
Adj. R-squared 0.333 0.403 0.349 0.417 0.354 0.423
Mean VIF 3.02 3.11 2.93 3.04 2.95 3.05
44
Table 12. Regressions of systemic risk (SES) and bank characterstics This sample includes CEO compensation contract information of all bank holding companies. The dependent variable is systemic risk measured in SES. The independent variables include the model-implied level of managerial risk-aversion with a range restriction of [0, 20], CEO age, non-firm wealth, wage, stock grants, option grants, stock ownership, option ownership, option moneyness, the natural logarithm of total assets, financial leverage, market to book, liquidity, return on asset, annual stock return, loan portfolios, and loan commitment. All specifications include year fixed-effects with clustered standard errors on the year level. t-statistics are shown in the parentheses with ***, ** and * indicating its statistical significant level of 1%, 5% and 10% respectively. Dependent Variable: SES (1) (2) (3) (4) (5) (6)
Risk Aversion -0.00518 (-0.67)
-0.00552 (-0.68)
-0.00358 (-0.46)
-0.00389 (-0.48)
-0.00344 (-0.44)
-0.00482 (-0.56)
Age
-0.0110 (-1.65)
-0.0111* (-2.01)
-0.00711 (-1.16)
-0.00853 (-1.70)
Wealth
-0.00190** (-2.59)
-0.00195*** (-2.91)
-0.00216** (-2.19)
-0.00253*** (-2.88)
Wage
0.00376 (0.16)
0.0171 (0.75)
Stock Grants
-2.301 (-1.07)
-2.106 (-0.85)
Option Grants
0.209 (0.53)
0.286 (0.65)
Stock Ownership to Total Shares
-0.0373** (-2.24)
-0.0289* (-1.88)
Option Ownership to Total Shares
0.0205 (0.38)
-0.00520 (-0.09)
In-The-Money of Owned Options
0.00693 (1.55)
0.00928* (1.99)
Natural Logarithm of Total Assets -0.0632 (-1.07)
-0.0109 (-0.19)
-0.0127 (-0.20)
0.0424 (0.71)
-0.0432 (-0.59)
0.00558 (0.08)
Financial Leverage -0.111*** (-3.94)
-0.0896*** (-3.37)
-0.108*** (-3.78)
-0.0913*** (-3.43)
-0.0895*** (-2.98)
-0.0780** (-2.77)
Market to Book -0.455*** (-4.20)
-0.381*** (-4.66)
-0.443*** (-4.48)
-0.371*** (-4.87)
-0.433*** (-4.81)
-0.385*** (-4.85)
Liquidity -0.0115 (-0.03)
0.543 (1.11)
-0.0508 (-0.12)
0.549 (1.11)
-0.186 (-0.45)
0.355 (0.73)
Return on Asset 31.80* (1.77)
33.01* (1.87)
37.17** (2.11)
37.86** (2.18)
39.57** (2.35)
40.29** (2.43)
Annual Stock Return 0.0102 (0.02)
0.100 (0.24)
0.0679 (0.15)
0.155 (0.37)
-0.0519 (-0.12)
0.0121 (0.03)
C&I Loans/Total Loans
1.101** (2.63)
1.013** (2.56)
0.750* (1.89)
Real estate Loans/Total Loans
1.627*** (2.99)
1.690*** (3.18)
1.576*** (3.28)
Agriculture Loans/Total Loans
-2.023 (-0.39)
-3.584 (-0.77)
-2.208 (-0.51)
Consumer Loans/Total Loans
2.206*** (4.24)
2.216*** (4.18)
2.024*** (4.07)
Non-performing Loans/Total Loans
-16.36** (-2.59)
-14.66** (-2.46)
-13.37** (-2.31)
Loan Commitment
0.0411 (0.07)
0.0855 (0.15)
0.106 (0.19)
N 561 561 561 561 561 561
Adj. R-squared 0.694 0.710 0.698 0.714 0.703 0.717
Mean VIF 3.02 3.11 2.93 3.04 2.95 3.05
45
Table 13. Regressions of systemic risk (ΔCoVaR) with bank fixed-effects This sample includes CEO compensation contract information of all bank holding companies. The dependent variable is systemic risk measured in ΔCoVaR. The independent variables include the model-implied level of managerial risk-aversion with a range restriction of [0, 20], CEO age, non-firm wealth, wage, stock grants, option grants, stock ownership, option ownership, option moneyness, the natural logarithm of total assets, financial leverage, market to book, liquidity, return on asset, annual stock return, loan portfolios, and loan commitment. All specifications include year and bank fixed-effects with clustered standard errors on the bank level. t-statistics are shown in the parentheses with ***, ** and * indicating its statistical significant level of 1%, 5% and 10% respectively. Dependent Variable: ΔCoVaR (1) (2) (3) (4) (5) (6)
Risk Aversion -0.00259 (-0.47)
-0.00203 (-0.37)
-0.00287 (-0.52)
-0.00262 (-0.47)
-0.00236 (-0.44)
-0.00309 (-0.56)
Age
0.00662 (1.40)
0.00840* (1.87)
0.00732 (1.50)
0.00883* (1.98)
Wealth
-0.000480 (-1.24)
-0.000379 (-1.00)
-0.000710* (-1.73)
-0.000499 (-1.23)
Wage
0.0178 (1.62)
0.0127 (1.04)
Stock Grants
0.383 (0.32)
0.0185 (0.02)
Option Grants
0.160 (0.96)
0.0912 (0.58)
Stock Ownership to Total Shares
-0.00789 (-0.92)
-0.00265 (-0.34)
Option Ownership to Total Shares
-0.0171 (-0.38)
-0.0340 (-0.71)
In-The-Money of Owned Options
-0.000511 (-0.17)
-0.00196 (-0.67)
Natural Logarithm of Total Assets -0.127* (-1.77)
-0.195*** (-2.70)
-0.122* (-1.83)
-0.198*** (-3.01)
-0.121* (-1.68)
-0.200*** (-2.67)
Financial Leverage -0.0177 (-0.56)
-0.0251 (-0.83)
-0.0175 (-0.55)
-0.0238 (-0.80)
-0.0134 (-0.45)
-0.0229 (-0.79)
Market to Book -0.0728 (-1.42)
-0.0705 (-1.49)
-0.0640 (-1.32)
-0.0626 (-1.44)
-0.0626 (-1.16)
-0.0559 (-1.15)
Liquidity 0.0911 (0.22)
0.112 (0.28)
0.0849 (0.22)
0.109 (0.29)
0.0829 (0.21)
0.120 (0.31)
Return on Asset 0.863 (0.12)
-2.224 (-0.32)
0.897 (0.14)
-2.284 (-0.34)
2.035 (0.30)
-1.562 (-0.22)
Annual Stock Return 0.0786 (0.98)
0.0625 (0.78)
0.0733 (0.91)
0.0548 (0.68)
0.0488 (0.53)
0.0621 (0.67)
C&I Loans/Total Loans
0.0420 (0.11)
0.0518 (0.14)
-0.0273 (-0.07)
Real estate Loans/Total Loans
0.886** (2.02)
0.873** (2.09)
0.813* (1.92)
Agriculture Loans/Total Loans
-14.66*** (-2.85)
-15.37*** (-2.99)
-15.20*** (-2.90)
Consumer Loans/Total Loans
-0.00264 (-0.01)
-0.0533 (-0.12)
-0.0652 (-0.14)
Non-performing Loans/Total Loans
1.247 (0.30)
0.898 (0.23)
1.001 (0.25)
Loan Commitment
0.212 (0.49)
0.274 (0.62)
0.327 (0.67)
N 561 561 561 561 561 561
Adj. R-squared 0.916 0.919 0.917 0.920 0.917 0.920
Mean VIF 4.75 8.48 4.80 8.56 5.18 9.08
46
Table 14. Regressions of systemic risk (SES) with bank fixed-effects This sample includes CEO compensation contract information of all bank holding companies. The dependent variable is systemic risk measured in SES. The independent variables include the model-implied level of managerial risk-aversion with a range restriction of [0, 20], CEO age, non-firm wealth, wage, stock grants, option grants, stock ownership, option ownership, option moneyness, the natural logarithm of total assets, financial leverage, market to book, liquidity, return on asset, annual stock return, loan portfolios, and loan commitment. All specifications include year and bank fixed-effects with clustered standard errors on the bank level. t-statistics are shown in the parentheses with ***, ** and * indicating its statistical significant level of 1%, 5% and 10% respectively. Dependent Variable: SES (1) (2) (3) (4) (5) (6)
Risk Aversion -0.00811 (-0.85)
-0.00524 (-0.57)
-0.00730 (-0.76)
-0.00485 (-0.53)
-0.00933 (-0.94)
-0.00674 (-0.75)
Age
-0.00302 (-0.21)
-0.00293 (-0.22)
-0.00646 (-0.47)
-0.00718 (-0.54)
Wealth
-0.00101 (-0.78)
-0.000555 (-0.46)
-0.00185 (-1.38)
-0.00131 (-1.04)
Wage
0.0511* (1.72)
0.0425 (1.33)
Stock Grants
-3.985 (-1.18)
-3.533 (-1.09)
Option Grants
0.161 (0.22)
0.108 (0.15)
Stock Ownership to Total Shares
-0.0141 (-0.26)
-0.00592 (-0.13)
Option Ownership to Total Shares
0.148 (1.12)
0.132 (1.01)
In-The-Money of Owned Options
0.00922 (1.32)
0.00966 (1.30)
Natural Logarithm of Total Assets -0.123 (-0.51)
-0.244 (-1.00)
-0.0884 (-0.37)
-0.220 (-0.92)
-0.123 (-0.47)
-0.227 (-0.84)
Financial Leverage 0.0199 (0.32)
0.00460 (0.06)
0.0176 (0.28)
0.00407 (0.06)
0.0339 (0.51)
0.0189 (0.25)
Market to Book -0.287** (-2.03)
-0.312** (-2.17)
-0.270** (-1.98)
-0.302** (-2.12)
-0.304** (-2.30)
-0.340** (-2.38)
Liquidity 0.170 (0.14)
0.346 (0.29)
0.0605 (0.05)
0.262 (0.22)
-0.000277 (-0.00)
0.208 (0.17)
Return on Asset 74.81*** (3.23)
70.08*** (3.03)
75.55*** (3.24)
70.70*** (3.04)
77.78*** (3.41)
73.37*** (3.23)
Annual Stock Return -0.0259 (-0.07)
0.00345 (0.01)
-0.0207 (-0.06)
0.00730 (0.02)
-0.212 (-0.65)
-0.156 (-0.49)
C&I Loans/Total Loans
1.248 (0.63)
1.205 (0.62)
1.081 (0.55)
Real estate Loans/Total Loans
3.067 (1.36)
2.980 (1.37)
2.582 (1.26)
Agriculture Loans/Total Loans
-7.957 (-0.59)
-7.527 (-0.56)
-3.603 (-0.26)
Consumer Loans/Total Loans
3.506 (1.59)
3.503 (1.60)
3.362 (1.55)
Non-performing Loans/Total Loans
-7.438 (-0.75)
-7.427 (-0.76)
-6.215 (-0.66)
Loan Commitment
-0.563 (-0.47)
-0.511 (-0.40)
-0.575 (-0.46)
N 561 561 561 561 561 561
Adj. R-squared 0.770 0.773 0.770 0.773 0.772 0.773
Mean VIF 4.75 8.48 4.80 8.56 5.18 9.08
47
Table 15. Regressions of systemic risk (ΔCoVaR) and alternative measure of CEO wealth This sample includes CEO compensation contract information of all bank holding companies. The dependent variable is systemic risk measured in ΔCoVaR. The independent variables include the model-implied level of managerial risk-aversion with a range restriction of [0, 20], CEO age, non-firm wealth, wage, stock grants, option grants, stock ownership, option ownership, option moneyness, the natural logarithm of total assets, financial leverage, market to book, liquidity, return on asset, annual stock return, loan portfolios, and loan commitment. All specifications include year and bank fixed-effects with clustered standard errors on the bank level. t-statistics are shown in the parentheses with ***, ** and * indicating its statistical significant level of 1%, 5% and 10% respectively. Dependent Variable: ΔCoVaR (1) (2) (3) (4) (5) (6)
Risk Aversion -0.000862
(-0.24) -0.00192 (-0.46)
-0.00118 (-0.32)
-0.00203 (-0.47)
-0.00120 (-0.32)
-0.00240 (-0.55)
Age
0.00698 (1.48)
0.00713 (1.48)
0.00710* (1.66)
0.00680 (1.56)
Wealth
-0.00106 (-0.52)
-0.00104 (-0.54)
-0.00241 (-1.17)
-0.00244 (-1.21)
Wage
0.0222** (2.12)
0.0239* (1.93)
Stock Grants
0.339 (0.38)
0.0688 (0.08)
Option Grants
0.248* (1.73)
0.209 (1.50)
Stock Ownership to Total Shares
-0.0216* (-1.75)
-0.0209 (-1.66)
Option Ownership to Total Shares
0.0463 (0.99)
0.0451 (0.95)
In-The-Money of Owned Options
0.000415 (0.16)
-0.000273 (-0.10)
Natural Logarithm of Total Assets -0.123** (-2.13)
-0.143** (-2.36)
-0.127** (-2.14)
-0.149** (-2.36)
-0.120* (-1.95)
-0.138** (-2.10)
Financial Leverage 0.0122 (0.63)
0.0108 (0.52)
0.0101 (0.53)
0.00807 (0.40)
0.0223 (1.25)
0.0203 (1.09)
Market to Book -0.0570* (-1.96)
-0.0539** (-2.02)
-0.0516* (-1.84)
-0.0482* (-1.84)
-0.0639* (-1.98)
-0.0570* (-1.82)
Liquidity 0.330 (0.84)
0.297 (0.76)
0.340 (0.89)
0.319 (0.83)
0.334 (0.95)
0.326 (0.93)
Return on Asset 1.339 (0.20)
1.426 (0.20)
0.996 (0.15)
0.901 (0.13)
1.103 (0.17)
1.208 (0.18)
Annual Stock Return 0.0943 (1.26)
0.0918 (1.21)
0.0818 (1.07)
0.0784 (1.02)
0.0518 (0.63)
0.0500 (0.60)
C&I Loans/Total Loans
-0.265 (-0.86)
-0.214 (-0.65)
-0.337 (-0.96)
Real estate Loans/Total Loans
0.472 (1.12)
0.476 (1.13)
0.430 (1.03)
Agriculture Loans/Total Loans
-3.325 (-1.09)
-4.179 (-1.31)
-2.607 (-0.84)
Consumer Loans/Total Loans
-0.298 (-0.59)
-0.329 (-0.64)
-0.218 (-0.43)
Non-performing Loans/Total Loans
0.264 (0.08)
0.220 (0.06)
0.640 (0.21)
Loan Commitment
0.606 (1.39)
0.536 (1.16)
0.458 (0.99)
N 622 622 622 622 622 622
Adj. R-squared 0.924 0.925 0.924 0.925 0.926 0.927
Mean VIF 3.95 5.21 3.99 5.26 4.47 5.72
48
Table 16. Regressions of systemic risk (SES) and alternative measure of CEO wealth This sample includes CEO compensation contract information of all bank holding companies. The dependent variable is systemic risk measured in SES. The independent variables include the model-implied level of managerial risk-aversion with a range restriction of [0, 20], CEO age, non-firm wealth, wage, stock grants, option grants, stock ownership, option ownership, option moneyness, the natural logarithm of total assets, financial leverage, market to book, liquidity, return on asset, annual stock return, loan portfolios, and loan commitment. All specifications include year and bank fixed-effects with clustered standard errors on the bank level. t-statistics are shown in the parentheses with ***, ** and * indicating its statistical significant level of 1%, 5% and 10% respectively. Dependent Variable: SES (1) (2) (3) (4) (5) (6)
Risk Aversion 0.00208 (0.21)
0.000290 (0.03)
0.00287 (0.29)
0.000464 (0.05)
-0.00113 (-0.10)
-0.00364 (-0.35)
Age
-0.0184 (-1.31)
-0.0215 (-1.39)
-0.0223 (-1.50)
-0.0250 (-1.54)
Wealth
0.00259 (0.51)
0.00262 (0.54)
0.00188 (0.34)
0.00150 (0.28)
Wage
0.0154 (0.36)
0.0243 (0.53)
Stock Grants
-2.167 (-0.90)
-2.073 (-0.87)
Option Grants
-0.389 (-0.82)
-0.399 (-0.81)
Stock Ownership to Total Shares
0.0795*** (3.89)
0.0724*** (3.46)
Option Ownership to Total Shares
0.0263 (0.23)
0.0292 (0.24)
In-The-Money of Owned Options
-0.00421 (-0.48)
-0.00376 (-0.40)
Natural Logarithm of Total Assets -0.159 (-0.87)
-0.179 (-0.85)
-0.147 (-0.73)
-0.160 (-0.69)
-0.113 (-0.51)
-0.144 (-0.57)
Financial Leverage 0.0492 (0.61)
0.0577 (0.70)
0.0548 (0.67)
0.0658 (0.79)
0.0420 (0.49)
0.0532 (0.62)
Market to Book -0.122 (-1.12)
-0.136 (-1.21)
-0.136 (-1.19)
-0.152 (-1.31)
-0.115 (-1.13)
-0.133 (-1.23)
Liquidity -0.203 (-0.20)
-0.315 (-0.29)
-0.233 (-0.24)
-0.388 (-0.37)
-0.339 (-0.33)
-0.503 (-0.45)
Return on Asset 53.26** (2.16)
52.99** (2.13)
54.18** (2.21)
54.60** (2.20)
60.06** (2.45)
60.10** (2.43)
Annual Stock Return 0.145 (0.43)
0.177 (0.52)
0.177 (0.53)
0.216 (0.63)
0.222 (0.66)
0.248 (0.72)
C&I Loans/Total Loans
-0.812 (-0.51)
-0.959 (-0.57)
-1.111 (-0.65)
Real estate Loans/Total Loans
0.393 (0.27)
0.389 (0.27)
0.349 (0.23)
Agriculture Loans/Total Loans
0.857 (0.10)
3.405 (0.38)
1.926 (0.22)
Consumer Loans/Total Loans
1.997 (1.21)
2.108 (1.28)
1.582 (0.94)
Non-performing Loans/Total Loans
-8.028 (-1.07)
-7.812 (-1.09)
-5.481 (-0.70)
Loan Commitment
0.157 (0.14)
0.373 (0.32)
0.652 (0.57)
N 622 622 622 622 622 622
Adj. R-squared 0.924 0.925 0.924 0.925 0.926 0.927
Mean VIF 3.95 5.21 3.99 5.26 4.47 5.72