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Does Analyst Forecasting Behavior Explain Anomalous Stock Market Reactions to Information in Cash and Accrual Earnings Components?
Dana Holliea, Phil Shaneb, Qiuhong Zhaoc
a Louisiana State University b University of Virginia and University of Auckland
cUniversity of Missouri at Columbia
Abstract
This study examines whether analysts’ forecasting behavior can explain market inefficiencies with respect to cash and accrual earnings components. Specifically, we focus on whether analysts’ earnings forecasts impound persistence characteristics of the retained and distributed free cash flow components of cash, and the sales growth and efficiency change components of accruals. In a sample of relatively large firms in recent years, our evidence points toward generalized analyst underreaction across all earnings components, market underreaction to the distributed-to-debtholder component of cash, and market overreaction to the efficiency change component of accruals. Our findings are consistent with misunderstanding of the implications of leverage changes for earnings persistence. Our findings are also consistent with accounting distortions that fool investors but not financial analysts. While we find no evidence that analyst behavior explains market overreaction to accruals, we estimate that analyst behavior can explain 35% of market underreaction to the distributed-to-debtholder component of cash.
JEL classification: G14, M41
Keywords: Analyst Forecast, Accruals, Cash Flows, Market Efficiency
We thank the Leeds School of Business for the Hart Fellowship support in 2007. We thank I/B/E/S for providing the analysts forecast data for this study. We would also like to thank Katherine Gunny, Steve Rock and workshop participants at Colorado State University, the University of Colorado at Boulder, the 2008 Annual AAA meeting and our discussant Sudipta Basu for their helpful comments. Qiuhong Zhao thanks the Leeds School of Business for the Hart Summer Fellowship support. * Email addresses: [email protected] (D. Hollie), [email protected] or [email protected] (P. Shane), and [email protected] (Q. Zhao).
1
I. Introduction
As information intermediaries financial analysts play an important role in conveying
information to the stock market.1
Building on prior research (e.g., Richardson et al., 2001; Richardson et al., 2005; and
Dechow et al., 2008), we examine analyst efficiency with respect to earnings disaggregated into
cash and accrual components, with the accruals portion further disaggregated into asset
efficiency change and sales growth components, and the cash portion further disaggregated into
distributed and retained components. Given that we evaluate analysts’ forecasts, our sample
necessarily differs from the samples used in prior studies of investor, but not analyst, response to
For that reason, whether analysts efficiently process
accounting information remains an interesting research question. This paper investigates whether
financial analysts’ forecasting behavior is a potential explanation for anomalous market response
to information in cash and accrual earnings components. Comparatively little prior research
evaluates the efficiency of financial analysts' earnings forecasts with respect to information in the
cash flow and accrual components of earnings, and even less research evaluates the degree to
which the behavior of analysts' earnings forecasts might explain accrual and cash flow
anomalies. The purpose of this paper is to evaluate analyst forecasting behavior as a potential
explanation for apparent stock market inefficiencies with respect to disaggregated cash and
accrual components of accounting earnings. Our two primary research questions are: Do analysts
efficiently process information in components of earnings? Does analyst forecasting behavior
explain market inefficiencies with respect to information in components of cash and accrual
earnings? Moreover, this study is the first to examine analysts’ ability to differentiate between
the persistence of the retained and distributed components of cash earnings.
1 See Schipper (1991), Brown (1993) and Ramnath et al. (2008) for literature reviews describing the role of financial analysts in capital markets.
2
information contained in earnings components. In particular, relative to the prior returns-oriented
research, our sample is constrained to more recent years and larger firms included in the I/B/E/S
database. Nonetheless, we are able to replicate the key prior research findings that the market
appears to overreact to the total accruals component of earnings and, in particular, to the portion
of accruals due to changes in asset efficiency.2
Contrary to Dechow et al., in our more recent sample of larger firms, we find that retained
cash earnings are as persistent as distributed cash earnings, and we find that the market appears
to: (i) react efficiently to the persistence of retained and distributed-to-stockholder cash earnings;
and (ii) underreact to the persistence of distributed-to-debtholder cash earnings. On the other
hand, Dechow et al. (2008) find that the market appears to react efficiently to the distributed
portion of cash earnings and overreact to the persistence of the retained portion of cash
earnings.
3 Clearly, differences in sample characteristics may play a role in differences between
the evidence in our study and Dechow et al. (2008). Although beyond the scope of our study,
future research might explore the influence of firm-size and analyst following on the relative
persistence of retained versus distributed cash earnings, distributed-to-stockholder versus
distributed-to-debtholder cash earnings, and market efficiency with respect to all three
components.4
2 Our evidence that efficiency changes drive the market overreaction to accrual earnings is in contrast to Hribar and Yehuda (2008), who provide evidence suggesting that accruals mispricing arises from misunderstanding of returns to the firm’s growth opportunities, particularly during the firm’s growth stage. Subsequent research might explore whether the sales growth versus efficiency change explanation for accruals mispricing depends on the stage of the firm in its life cycle.
3 However, as discussed below, our results are consistent with Dimitrov and Jain (2008) who find that the market underreacts to the association between increases in leverage and deteriorating operating performance. 4 Each earnings component can take on positive or negative values. For example, the distributed-to-debtholder component of cash earnings is positive in the case of net payments to debtholders (i.e., debt-reducing cash flows) or negative in the case of net receipts from debtholders (i.e., debt-increasing cash flows). Similarly, the change in asset efficiency and sales growth components of accrual earnings can take on positive or negative values, and both the retained and distributed-to-equity components of cash earnings can take on positive or negative values.
3
Additionally, we find that analysts appear to underreact to both cash and accrual components
of earnings. We also find similar analyst underreaction across all three cash components of
earnings (retained cash and cash distributed to both debtholders and stockholders). Furthermore,
we find that analyst underreaction to the sales growth (rather than the efficiency change)
component of accruals drives analysts’ overall underreaction to the persistence of accrual
earnings. Thus, we find no evidence that analyst forecasting behavior explains apparent market
overreaction to accrual earnings.5
Our evidence of analyst underreaction to accrual earnings is inconsistent with Bradshaw et al.
(2001), who find that analysts overreact to the persistence of working capital accruals in a
manner consistent with the market overreaction observed in Sloan (1996). However, our results
are consistent with Yu (2007) who provides evidence that Bradshaw et al.’s (2001) omission of
the cash earnings variable explains the differences in results between the two studies. Since cash
and accrual earnings are negatively correlated, a positive relation between cash earnings and
subsequent forecast errors may explain the Bradshaw et al. (2001) finding that accruals are
negatively related to future forecast errors. In fact, when we omit the cash variable, consistent
with Bradshaw et al. (2001), we find a negative correlation between accruals and future forecast
errors. However, when we include the cash variable, consistent with Yu (2007), we find that
analysts’ forecasts underreact to the persistence of accrual earnings.
Our evidence of analyst underreaction to the net distribution-
to-debtholders component of cash earnings is consistent with our evidence of similar market
underreaction. However, our empirical findings provide evidence of a point estimate that only
35% of the market underreaction can be attributed to analyst underreaction.
5 This interpretation is consistent with Hughes et al. (forthcoming) who find that trading strategies based on predictable analyst forecast errors are not profitable.
4
Our empirical results, suggesting that analysts generally underreact to earnings persistence
across all components of accruals and cash flows, are consistent with the theory of analyst
underreaction developed in Raedy et al. (2006). Raedy et al. (2006) develop a mathematical
model predicting generalized analyst underreaction, given an asymmetric loss function that
punishes analysts more severely for reversing the direction of their earnings forecasts in light of
new information. This view suggests that analysts are sophisticated users of financial accounting
information and, as such, understand the persistence properties of various earnings components.
However, economic incentives lead analysts to underreact, and the underreaction is apparent
across all earnings components.6 On the other hand, the market includes unsophisticated
investors, who apparently overreact to the persistence of some accrual earnings components and
underreact to some cash earnings components, and market frictions prevent sophisticated
arbitragers from fully exploiting these inefficiencies.7
The rest of the paper is organized as follows. The next section discusses prior research, and
section III describes our research design. Section IV describes our sample, section V presents our
results, and section VI summarizes and concludes the paper.
II. Prior Research
6 Also, see Francis and Philbrick (1993) who find evidence suggesting that economic incentives lead analysts to bias their earnings forecasts upward in the face of bad news, and see Trueman (1990) who develops a mathematical model suggesting that analysts rationally underreact to public information to disguise relatively low ability in developing timely private information. 7 Lev and Nissim (2006) and Mashruwala et al. (2006) indicate that the accrual anomaly persists and will probably endure. The explanation for why the accrual anomaly is not arbitraged away by sophisticated institutional investors is that institutions avoid extreme-accrual firms because of their attributes, such as small size, low profitability, and high risk and that sophisticated individual investors are unable to profit from trading on accruals information due to the high information and transaction costs. Also see Hirshleifer and Teoh (2003) who argue that non-diversifiable risk associated with trading against inefficient unsophisticated investor behavior limits sophisticated investor arbitrage trading that might otherwise eliminate the mispricing.
5
Beginning with Sloan (1996), researchers have investigated stock market efficiency with
respect to information in accrual and cash flow components of earnings. While Sloan examined
the market’s response to operating cash flows and working capital accruals minus depreciation,
the research has evolved to consider the market response to total accruals, accruals disaggregated
into various components, and cash flows disaggregated into retained and distributed components.
Richardson et al. (2005) find that the market overreacts to the persistence of both current
(non-cash working capital) and non-current operating accruals and that trading strategies based
on total operating accruals generate more profits than strategies based on current operating
accruals. Richardson et al. (2001, 2006) disaggregate total operating accruals into sales growth
and asset efficiency (i.e., turnover) components. Richardson et al. (2001) find that the market
overreacts to the persistence of both the sales growth and asset efficiency change components of
total accruals. The authors interpret this result to support both the perspective of Fairfield et al.
(2003), Cooper et al. (2005) and others that the accrual anomaly emerges from diminishing
returns on firms' growth opportunities and the perspective of Sloan (1996), Xie (2001) and others
that the accrual anomaly emerges from accounting distortions. We extend this research by
examining whether analysts’ forecasting behavior can explain market inefficiency with respect to
total operating accruals, as well as the sales growth and asset efficiency change components of
total operating accruals.
Dechow et al. (2008) disaggregate the cash component of earnings and find that the market
reacts efficiently to the persistence of the portion of cash earnings that the firm distributes to
investors; whereas, the market overreacts to the persistence of the portion of cash earnings that
the firm retains. This contradicts prior research evidence that the market underreacts to total cash
earnings (e.g., Sloan 1996; Desai et al., 2004; Ahmed et al. 2006). In a sample of larger firms
6
followed by analysts during a more recent time period, we re-examine the market's response to
cash components of earnings, and extend the literature by examining whether analysts’
forecasting behavior can explain the market’s response to the cash components of earnings as
defined in Dechow et al. (2008). Contrary to Dechow et al. (2008), but consistent with Dimitrov
and Jain (2008) and Penman et al. (2007), we find that the market underreacts to the persistence
of the distributed-to-debtholder component of cash earnings. As described by Dimitrov and Jain
(2008), if managers have private information about deteriorating operating performance, they
may increase debt to provide funds to replace anticipated shortfalls. Dimitrov and Jain (2008)
provide evidence that the market appears to underreact to the negative signal about future
performance associated with current increases in debt (which, in our study, corresponds to a
negative distributed-to-debtholder component of cash earnings). Our evidence that the market
underreacts to the persistence of the distributed-to-debtholder component of current cash
earnings is consistent with the evidence and discussion in Dimitrov and Jain (2008). Similarly,
Penman et al. (2007) find a negative relation between the leverage component of the book-to-
price ratio and subsequent stock returns.8
8 Bradshaw, Richardson, and Sloan (2006) identify two competing hypotheses about the relationship between future stock returns and changes in debt: Ritter’s (2003) misvaluation hypothesis and Eberhart and Siddique’s (2002) wealth transfer hypothesis. Consistent with Bradshaw et al. (2006), our evidence of a positive relation between the distributed-to-debtholder component of cash earnings and both subsequent analyst forecast errors and subsequent stock return performance supports the misvaluation hypothesis. That is, our evidences suggests that analysts’ forecasts and stock prices are too low (high) following distributions to (from) debtholders, which means decreases (increases) in debt lead to positive (negative) future returns and forecast errors (consistent with Bradshaw et al.).
In addition to reexamining the persistence and market
reaction to information in cash earnings components, our study investigates the efficiency of
analysts’ earnings forecasts with respect to information in cash earnings components, and we
also investigate analyst forecasting behavior as an explanation for market inefficiencies with
respect to disaggregated cash earnings.
7
8
III. Research design
Our investigation of analyst and investor response to cash and accrual earnings
components, respectively, builds on earnings disaggregations developed by Richardson et al.
(2001, 2006) and Dechow et al. (2008). Consistent with Dechow et al. (2008), we disaggregate
earnings into free cash flow (cash) and accrual components as follows (firm subscripts
suppressed throughout all models):
RNOAt = FCFt + ΔNOAt (1)
where RNOAt = operating income after depreciation, FCFt = free cash flow, and ΔNOAt = total
operating accruals, all deflated by NOAt-1 (non-cash net operating assets).9
FCFt = ΔCASHt + DIST_Dt + DIST_EQt (2)
Dechow et al. (2008)
disaggregate FCFt (cash earnings) into retained and distributed components as follows:
where ΔCASHt = the change in cash and short-term investments (i.e., free cash flow retained),
DIST_Dt = free cash flow to debtholders (excluding interest), and DIST_EQt = free cash flow to
stockholders (net income minus the change in stockholders’ equity), all deflated by NOAt-1.10
Consistent with Richardson et al. (2001, 2006), we define and disaggregate total
operating accruals as follows:
ACCt = SGt – ΔEFFt – (SGt * ΔEFFt) (3)
where: ACCt represents total operating accruals, defined as the percentage change in the firm’s
net operating assets; SGt = ΔSalest/Salest-1 and represents sales growth; ΔEFFt = ΔATt/ATt and
represents the change in asset efficiency measured as (Salest/NOAt – Salest-1/NOAt-1) /
(Salest/NOAt); and NOAt = total non-cash current and non-current operating assets less total
9 Theoretically, RNOAt in (1) should be NOIt (i.e., net operating income after tax). Following Richardson et al. (2005, 2006), we simply represent RNOAt as income after depreciation (Compustat item # 178). 10 Theoretically, distributions to preferred stockholders should be included in DIST_D. Following Dechow et al., we include distributions to/from preferred stockholders in DIST_EQ.
9
current and non-current operating liabilities (with cash treated as a financial asset). Richardson et
al. (2006) provide an algebraic proof showing that the three terms on the RHS of (3) sum to total
accruals (ACCt).11 The authors argue that this decomposition allows tests with the potential to
distinguish between two competing explanations for the accrual anomaly: market failure to fully
impound mean reversion in sales growth versus market failure to fully impound information in
accruals about temporary accounting distortions. If diminishing marginal returns on investment
drive the lower persistence of accruals, this should be reflected in the growth component (SGt).
In contrast, if accounting distortions or changes in real operating efficiency drive the lower
persistence of accruals, then this should be reflected in the efficiency component (EFFt).12
Summarizing (1), (2), and (3) above, our fully disaggregated model of net income
becomes:
RNOAt = (ΔCASHt + DIST_Dt + DIST_EQt)
+ [SGt – ΔEFFt – (SGt * ΔEFFt)] (4)
where the first bracketed term on the RHS of (4) disaggregates free cash flow (FCFt), and the
second bracketed term disaggregates accruals (ACCt). Following Dechow et al. (2008), we
examine the persistence of the various earnings components by replacing RNOAt in model (4)
with RNOAt+1 in the summary components and detailed components regression models (5) and
(6) below.
RNOAt+1 = θ0 + θ1 FCFt + θ2 ACCt + ηt+1 (5) 11 Appendix A provides detailed definitions of each variable used in the study, along with Compustat item numbers. 12 Results in Hribar and Yehuda (2008) suggest that market overreaction to the persistence of firms’ growth opportunities, rather than overreaction to the persistence of accounting accruals, drives the accruals anomaly, particularly for growth firms early in their life cycle. If this is the case, then we expect that, controlling for market reaction to cash earnings components, the sales growth component should drive any market overreaction to accruals. Our results do not support this prediction and, instead, suggest that the market overreaction to accruals is driven by overreaction to the persistence of the changes in asset efficiency component, rather than the sales growth component, of total accruals.
10
RNOAt+1 = λ0 + λ1∆CASHt + λ2DIST_EQt + λ3DIST_Dt
+ λ4SGt + λ5ΔEFFt + λ6(SGt * ΔEFFt) + ξt+1 (6)
Positive θ1 and θ2 in model (5) indicate that the summary earnings components, FCFt and ACCt,
respectively, are positively related to future earnings (i.e., they persist). Positive λ1, λ2, λ3, and λ4
and negative λ5 in model (6) indicate that the detailed earnings components, ∆CASHt, DIST_EQt,
DIST_Dt, SGt, and ΔEFFt, respectively, are positively related to future earnings (i.e., they
persist).
Next, we evaluate market efficiency with respect to the various components of cash and
accrual earnings.
RETt+1 = α0 + α1FCFt + α2ACCt + ut+1 (7)
RETt+1 = γ0 + γ1(ΔCASHt ) + γ2(DIST_EQt) + γ3(DIST_Dt)
+ γ4(SGt) + γ5(ΔEFFt) + γ6(SGt*ΔEFFt) + et+1 (8)
where RETt+1 = firm i’s raw returns, accumulated from the fifth month following the end of
fiscal year t through the fourth month following the end of fiscal year t+1, minus the similarly
accumulated mean return of all firms in the same size-decile as firm i (with size deciles formed
as of the end of fiscal year t).13
13 For sensitivity analysis, we accumulate returns starting from the beginning of the fourth month following the end of fiscal. The results are qualitatively the same.
All empirical models exclude firm-year observations with
negative values of NOAt-1 and, following Richardson et al. (2005), all financial statement ratios
are winsorized at +/-1 to mitigate the influence of outliers. If, as described in Richardson et al.
(2001), stock prices overreact to the persistence of sales growth and efficiency components of
11
total accruals, then we expect α2 < 0 in (7) above, and we expect γ4 < 0 and γ5 > 0 in (8) above.14
If, as described in Dechow et al. (2008), stock prices overreact to the persistence of the retained
component of cash earnings, then we expect γ1 < 0 in (8) above.15
To evaluate any inefficiency in analysts’ earnings forecasts following the release of
financial statement information containing cash and accrual earnings components, we estimate
summary model (9) and components model (10) below.
FEt+1 = β0 + β1FCFt + β2ACCt + εt+1 (9)
FEt+1 = δ0 + δ1(ΔCASHt) + δ2(DIST_EQt) + δ3(DIST_Dt)
+ δ4(SGt) + δ5(ΔEFFt) + δ6(SGt*ΔEFFt) + ωt+1 (10)
where FEt+1 = (At+1 – Ft+1) / Pt ; At+1 = actual earnings for year t+1 per I/B/E/S; Ft+1 is the most
recent individual analyst forecast of year t+1 earnings, released prior to the beginning of the
return accumulation period; and Pt is the adjusted price taken from the same I/B/E/S monthly
report containing Ft+1.16
14 Controlling for sales growth, increases in asset efficiency (ΔEFFt) correspond to decreases in NOAt and decreases in accruals [see model (3) above]. Thus, if investors overreact to the persistence of accruals components of earnings, then increases in ΔEFFt (and decreases in accruals) should correspond to lower stock prices, higher subsequent returns (as correction occurs), and γ5 > 0 in model (8).
If analysts issue efficient forecasts following firms’ release of their
financial statements containing cash and accrual components of earnings, then the information in
those financial statements should not predict analysts’ forecast errors (FEt+1), and the coefficients
on the information variables in (9) and (10) should equal zero. The intercept term (β0 or δ0)
15 Rather than using the framework developed by Mishkin (1983), we use a conventional OLS model to test the rational expectations hypotheses. Kraft et al. (2007) show that OLS and the Mishkin test generate identical inferences in accounting settings when samples are large. As described in Kraft et al. (2007), to obtain estimates of the difference between actual and implied market estimates of the persistence of earnings components, the residual terms from models (5) and (6) are added as independent variables in models (7) and (8). Then the difference between actual and implied market persistence estimates are derived by dividing each component variable coefficient by the residual variable coefficient in models (7) and (8). 16 When more than one individual analyst forecast occurs on the day we use the median of those forecasts.
12
captures analysts’ optimism/pessimism. For example, a significantly negative coefficient for the
intercept term would indicate systematically optimistic analysts’ forecasts.
To assess whether analyst forecasting behavior potentially explains market inefficiencies
with respect to information in cash and accrual components of earnings, we estimate summary
model (11) and components model (12).
RETt+1 = ρ0 + ρ1FCFt + ρ2ACCt + ρ3FEt+1 + ρ4FREVt+2+ et+1 (11)
RETt+1 = φ0 + φ1(ΔCASHt) + φ2(DIST_EQt) + φ3(DIST_Dt)
+ φ4(SGt) + φ5(ΔEFFt) + φ6(SGt)*(ΔEFFt) + φ7FEt+1 + φ8FREVt+2 + μt+1 (12)
where FREVt+2 = (t+1Ft+2 – tFt+2) / Pt; t+1Ft+2 is the first individual analyst forecast of t+2 earnings
issued after the end of the return accumulation period; and tFt+2 is the most recent forecast of t+2
earnings issued prior to the beginning of the return accumulation period.
Following Richardson et al. (2001, 2005), we use models (7) and (8) above to assess market
efficiency with respect to earnings components in our sample and during our time period. If
analyst forecasting behavior explains market inefficiency with respect to the information in cash
and accrual components of earnings, then we expect the coefficients on the cash and accrual
earnings information variables in models (9) and (10) to have the same signs and similar
significance levels as the coefficients on the same information variables in models (7) and (8),
and we expect the coefficients on the same information variables in models (11) and (12) to
equal zero. As described in Shane and Brous (2001), if analyst forecasting behavior explains
market inefficiency with respect to information about future earnings, then adding the forecast
error and forecast revision variables to the returns regression should make the coefficients on the
information variables go to zero.
13
IV. Sample
Since we rely on I/B/E/S to measure the forecast error (FEt+1) and forecast revision
(FREVt+2) variables in models (9) through (12), our sample represents larger firms and a more
recent time period relative to the sample and time periods in Dechow et al. (2008) and
Richardson et al. (2001, 2005). Our time period spans the years 1988-2006; whereas, the
Richardson et al. (2001) time period spans 1988-1998, the Richardson et al. (2005) time period
spans 1962-2001, and the Dechow et al. (2008) time period spans 1950-2003.
To estimate the variables in our models, we obtain: financial statement data from Compustat;
returns data from CRSP; and earnings forecasts, actual earnings, and stock prices from I/B/E/S.
Table 1 describes our sample selection procedure. Our initial sample finds 186,928 firm-year
observations on Compustat’s Annual Industrial, Research, and Full Coverage files between the
years, 1988 and 2006. Following Richardson et al. (2005) and Richardson et al. (2006), we
exclude firms in the financial services industry (32,923 firm-years with SIC codes in the range
6000-6999). We omit 56,001 observations without Compustat data needed to compute our cash
flow and accrual earnings component variables or with negative net operating assets. We lose
29,649 observations missing the CRSP data needed to compute our returns variable. We lose
another 51,661 firm-year observations without I/B/E/S data needed to compute our forecast error
variable (FE), and we lose 7,929 observations without I/B/E/S data needed to compute our
forecast revision variable (FREV), resulting in a final sample of 8,755 firm-years spanning the
1988-2006 time-frame.
{Insert Table 1 about here}
14
V. Results
Descriptive statistics
Table 2 presents descriptive statistics, including univariate correlations between variables
used in the study. The sample firms exhibit relatively high sales growth (15.8% on average),
slightly optimistic analyst forecasts (FE < 0), and horizon-dependent optimism (FREV < 0).
Most firm-years are associated with distributions of cash to stockholders (median DIST_EQ =
0.109), increases in debt (median DIST_D = -0.002), and positive free cash flow (median FCF =
0.1). The latter result is inconsistent with Dechow et al. (2006) whose sample has a negative
median free cash flow (median FCF = -0.014). Negative free cash flow is not necessarily an
indication of a financially distressed firm. Many young firms put a lot of their cash into
investments, which diminishes their free cash flow. However, a firm should have a good reason
for having negative free cash flows and the firm should be earning a sufficiently high rate of
return on its investments. While free cash flow does not receive as much scrutiny as earnings, it
is considered by some experts to be a better indicator of a firm’s financial health. Dechow et al.
(2008) find that accruals are less persistent than cash flows, on average, only in their subsample
of negative FCF firm-years. While our sample is characterized by firms with relatively more
persistent accrual earnings, as described in table 3 below, we still find that cash earnings (FCF)
are more persistent than accrual earnings (ACC) in our sample.
{Insert Table 2 about here}
Panel B of Table 2 provides pair-wise correlations among the variables used in this study. On
a univariate basis, it appears that changes in asset efficiency, rather than sales growth, explain the
overall negative correlation between accruals and the subsequent year’s returns. Analysts also
appear to overestimate the persistence of the changes in asset efficiency earnings component, as
15
we observe a positive correlation between changes in asset efficiency and subsequent forecast
errors. Thus, on a univariate basis we see some indication that analyst forecasting behavior could
explain market overreaction to the persistence of the change in asset turnover component of
accrual earnings. The univariate correlations also provide some evidence of market and analyst
underreaction to the persistence of the distributed portion of free cash flow.
Table 3 describes returns to trading strategies with positions in top and bottom deciles of
each detailed earnings component: FCFt, ACCt, SGt, ΔEFFt, ΔCASHt, DIST_EQt and DIST_Dt.
Table 3 also describes differences in analyst forecast errors in the top versus bottom deciles of
the same variables. Panel A shows a 10.4% hedge portfolio return based on a trading strategy
taking a long (short) position in stocks in the highest (lowest) decile of cash earnings; however
this hedge return is not statistically significant, as the two-tailed p-value associated with the
difference in mean returns in the highest versus lowest decile is 0.14. Panel A shows that
analysts’ forecast errors are significantly larger in the highest decile relative to the lowest decile
of cash earnings. Thus, on a univariate basis, it appears that analysts’ forecasts underreact to the
persistence of cash earnings.
{Insert Table 3 about here}
Panel B shows a 13.2% hedge portfolio return based on a trading strategy taking a long
(short) position in stocks in the lowest (highest) decile of net operating accruals. Panels C and D
suggest that this 13.2% hedge portfolio return is driven by market overreaction to the efficiency
change component (ΔEFF) of net operating accruals. We find a statistically significant 12.4%
hedge portfolio return based on a trading strategy taking a long (short) position in stocks in the
highest (lowest) decile of ΔEFF. Recall that the highest decile contains stocks where asset
turnover increased due to either an increase in sales (holding net operating assets constant) or a
16
decrease in accruals (holding sales growth constant). Since, we see only a 0.2% return to a
trading strategy based on sales growth (panel C), we attribute the 12.4% return to the trading
strategy based on changes in asset efficiency to a denominator effect (i.e., changes in accruals,
holding sales growth constant). On the other hand, financial analysts’ earnings forecasts do not
differ significantly between the top and bottom deciles of total accruals (ACC) or accrual
components (SG, ΔEFF).
In our sample of relatively large profitable and positive free cash flow firms, contrary to
Dechow et al. (2008), we find no evidence of returns to a trading strategy based on the retained
cash component of free cash flow (panel E). We do, however, find some evidence (panel G) of
returns to a trading strategy taking long (short) positions in stocks with high (low) free cash flow
to debtholders (7.6%, p-value = 0.018). This suggests that the market efficiently impounds
(underreacts to) information about the persistence of the retained (distributed-to-debtholder)
component of cash earnings. On the other hand, our univariate tests suggest that financial
analysts’ earnings forecasts underreact to the persistence of the distributed-to-stockholder
component of cash earnings (panel F).
Returns analysis
Before examining market efficiency with respect to earnings components, we report the
persistence characteristics of earnings components for our sample firms and time period. Panel A
of Table 4 shows that the coefficients relating cash and accrual earnings to next year RNOA are
0.618 and 0.420, respectively, and both coefficients are highly significant. Similarly, as shown in
table 4 panel B, each detailed cash and accrual earnings component is strongly related to next
year’s RNOA, and all components have positive persistence.
17
{Insert Table 4 about here}
Table 5 describes the behavior of stock returns following publication of information in
accrual and cash components of earnings. In panel A, like Richardson et al. (2001, 2005), we
find a significantly negative relation between total accruals and following year returns,
suggesting market overreaction to the persistence of accrual earnings. Like Richardson et al.
(2001, 2005), we do not find a significant relation between cash earnings and subsequent returns.
Compared to Richardson et al. (2001, 2005), the coefficient on the total accruals variable is
smaller in our sample. We attribute this difference to mitigation of the negative relation between
accruals and subsequent returns during the 1999-2006 time period.17
{Insert Table 5 about here}
Panel B of Table 5 replicates the Richardson et al. (2001) analysis of the relation of cash
flow and disaggregated current fiscal year accrual earnings components with following year
returns. In both our replication and the Richardson et al. (2001) study, the cash flow component
of earnings is not significantly related to future returns, and the change in asset efficiency
component of accruals is positively related to future returns. In our sample, the coefficient on the
sales growth component of accruals although negative is not significantly different from zero;
whereas, Richardson et al. find a significantly negative relation between sales growth and
following year returns. The coefficient on the change in asset efficiency component of accruals is
only about half the size of the coefficient in the Richardson et al. (2001) study.18
17 Our results do not change when we remove our forecast error and forecast revision data constraint. However, when we maintain that constraint but eliminate the years 1999-2006, the estimated coefficient on the accruals variable is similar in magnitude than the coefficient in the Richardson et al. study.
Nonetheless,
using our smaller sample of larger firms in a more recent time period, we are able to replicate the
18 The analysis of the relation of future returns with current accruals disaggregated into sales growth and change in asset efficiency components appears only in the Richardson et al. (2001) working paper and not in any subsequent published papers.
18
Richardson et al. (2001) finding that the market apparently overreacts to the persistence of the
change in the efficiency component of total accruals.19
Panels C and D of Table 5 extend the analysis to include the relation between
disaggregated cash flow and accrual information and next year’s returns. Panel C shows that, in
our sample, we replicate the result in Dechow et al. (2008) that the market overreacts to the
persistence of the accrual component of current year earnings and, consistent with Richardson et
al. (2001), panel D shows the overreaction to ΔEFFt drives the overreaction to ACCt.
Panel D of Table 5 reports the results of estimating our full returns model (8), which
regresses following year abnormal returns (RETt+1) on all three current year cash components of
earnings (ΔCASH, DIST_EQ, and DIST_D) and all three current year accrual components of
earnings (SG, ΔEFF and SG*ΔEFF). Consistent with our results reported above, estimates of
coefficients of the full model (8) suggest that in our sample the market underreacts to the
persistence of the net distributed-to-debtholder cash earnings component (DIST_D); whereas
Dechow et al. (2008) find that the market overreacts to the persistence of the retained cash
earnings component (ΔCASH).
Analyst forecast errors
To assess the efficiency of analysts’ earnings forecasts following the release of financial
statements containing information about the cash and accrual components of the prior year’s
earnings, we estimate models (9) and (10). Table 6 reports estimates of our regressions of
analysts’ forecast errors on prior year cash and accrual components of earnings. Given the results
reported above, if analyst forecasting behavior is consistent with the market response to total and
19 Recall that, holding sales growth constant, an increase in asset turnover (efficiency) corresponds to a decrease in accruals, so a positive coefficient on the efficiency change variable indicates that the market has overreacted to the persistence of this component of accruals.
19
disaggregated cash and accrual earnings, then we expect a negative coefficient on total accruals
in model (9), a positive coefficient on the efficiency change component of accrual earnings in
model (10), and a positive coefficient on the distributed-to-debtholder component of cash
earnings in model (10).
{Insert Table 6 about here}
Panel A shows the results of estimating summary model (9), which regresses the error in
forecasts following the release of prior year financial statements on prior year cash (FCF) and
accrual (ACC) summary earnings components. The significantly positive coefficients on both
variables suggest that analysts’ earnings forecasts underreact to the persistence of both cash and
accrual earnings; whereas, we found in Table 5 that the market appears to overreact to the
persistence of accrual earnings. Thus, it does not appear that analyst forecasting behavior can
explain the apparent market overreaction to the persistence of accruals. Furthermore, panel B
indicates that the underreaction to accrual earnings extends to both the sales growth and asset
efficiency change components of total accruals, although the coefficient on the efficiency change
component is only marginally significant. Nonetheless, analyst behavior does not appear to be
responsible for investor overreaction to the persistence of the efficiency change component of
accrual earnings.
Panel C reports estimates of the coefficients in our full model (10). As shown in panel C,
analyst underreaction to cash earnings extends to all three components: ΔCASH, DIST_EQ, and
DIST_D. The positive coefficient on DIST_D offers a possible explanation for the market’s
underreaction to the distributed-to-debtholders component of cash earnings documented in panel
D of Table 5. Overall, we find that analyst behavior can only partially explain apparent market
inefficiencies in processing information about the persistence of accrual and cash earnings.
20
Analyst forecasting behavior as an explanation for market inefficiency
To summarize the results above, we find some evidence of market overreaction to total
accruals (panel A of Table 5), market overreaction to the asset efficiency change component of
total accruals (panel D of Table 5), and market underreaction to the distributed-to-debtholders
component of cash earnings (panel D of Table 5); and we find evidence of general analyst
underreaction to accrual and cash components of earnings, with the possible exception of the
efficiency change component of accruals (panel C of Table 6).
Table 7 adds forecast error and forecast revision variables to the returns summary and
component models estimated in Table 5. Like the returns variable, the forecast error (FE) and
forecast revision (FREV) variables are computed with reference to forecasts issued following
firms’ publication of financial statements containing the earnings component information
variables: ACC, SG, ΔEFF, FCF, ΔCASH, DIST_EQ, and DIST_D. If analyst forecasting
behavior explains the market overreaction to ACCt and ΔEFFt and the market underreaction to
DIST_Dt, then we expect the coefficients on those variables to approach zero when we add FEt+1
and FREVt+1 to the returns model.20
{Insert Table 7 about here}
As described in panel A of Table 7, without FEt+1 and FREVt+2 in model (7), the coefficient
relating ACCt to RETt+1 equals -0.062 and is significantly less than zero (p-value < 0.05). Since
estimating models (9) and (10) in Table 6 produces no evidence that analysts overreact to any
earnings components, it is not surprising that adding FEt+1 and FREVt+1 to model (7) does not
cause the coefficient on ACCt to move much towards zero. In fact, panel A of Table 7 shows that
20 See Shane and Brous (2001) for a detailed explanation of this approach to gauging the degree to which analyst forecasting behavior explains market inefficiencies.
21
the coefficient on ACCt in model (11) is -0.060, still significantly negative (p-value < 0.05).
Similarly, the coefficient relating ΔEFFt to RETt+1 equals 0.11 without FEt+1 and FREVt+1 in
model (8) (indicating market overreaction to the persistence of changes in asset efficiency, p-
value < 0.01), and adding FEt+1 and FREVt+2 to model (8) does not cause the coefficient on
ΔEFFt to move much towards zero. In fact, the coefficient on ΔEFFt in model (12) is 0.104, still
significant at less than the 0.01 level.
On the other hand, since the market underreacts to the persistence of DIST_Dt (panel D of
Table 6), and analysts similarly underreact (panel C of Table 6), we expect the coefficient on
DIST_Dt to move towards zero when we add FEt+1 and FREVt+2 to model (8). In fact, the
coefficient relating DIST_Dt to RETt+1 is 0.057 without FEt+1 and FREVt+2 in the model (p-value
< 0.05), and it decreases by 35% to 0.037 and is no longer statistically significant when we add
FEt+1 and FREVt+1 to the model. Thus, we estimate that analyst forecasting behavior potentially
explains 35% of the market’s underreaction to the distributed-to-debtholder component of cash
earnings.
VI. Conclusion
Richardson et al. (2001, 2005) provide evidence suggesting that stock prices overreact to the
persistence of total operating accruals, and Richardson et al. (2001) provide evidence that the
apparent stock price overreaction to the persistence of total operating accruals extends to two
important accrual earnings components: sales growth and change in asset efficiency. Dechow et
al. (2008) provide evidence that stock prices overreact to the persistence of cash earnings, and
Dechow et al. find that overreaction to the persistence of the retained cash component of
earnings drives the market’s overreaction to total cash earnings. Since both Dechow et al. (2008)
22
and Richardson et al. (2001) suggest that the market does not efficiently impound information
about the persistence of earnings components, an important question is whether financial
analysts fail to distinguish the persistence of various earnings components and, thereby, publish
earnings forecasts that create market inefficiency.
We find little evidence to support the view that financial analysts are responsible for market
inefficiency with respect to the persistence characteristics of the various earnings components
evaluated by Dechow et al. (2008) and Richardson et al. (2001). Instead, consistent with
economic theories of analyst underreaction (e.g., Raedy et al. 2006, Trueman 1990), we find a
generalized analyst underreaction to earnings components.
Our sample of relatively large firms followed by analysts in a recent time period produces
results that differ somewhat from the evidence of market inefficiencies in Dechow et al. (2008)
and Richardson et al. (2001). In particular, we do not find the overreaction to sales growth
documented by Richardson et al. (2001), and we find that the market underreacts to the
persistence associated with cash earnings distributed to debtholders, whereas, Dechow et al.
(2008) find that the market overreacts to cash earnings retained for reinvestment. Our evidence
is consistent with market underreaction to the persistence of earnings components corresponding
to cash flows that increase or decrease leverage. Our evidence is also consistent with accounting
distortions causing temporary accounting changes in asset efficiency (turnover) that fool
investors but not financial analysts.
23
Appendix A Variable definitions
(Firm i subscripts suppressed; Item #s refer to Compustat) RETt+1 = the annual buy and hold size-adjusted return. The size-adjusted return is calculated by subtracting the value-weighted average return for all firms in the same size-matched decile, where size is measured as market capitalization at the beginning of the return accumulation period. The return accumulation period begins four months after the end of fiscal year t. FEt+1 = the signed forecast error, calculated as (At+1 – Ft+1) / Pt. At+1 is actual earnings for fiscal year t+1, per I/B/E/S. Ft+1 is the most recent I/B/E/S individual forecast prior to the beginning of the return accumulation period. When more than one forecast occurs on that day, Ft+1 is the median of all forecasts occurring on that day. Pt is the adjusted price taken from the same I/B/E/S report month containing Ft+1. FREVt+2 = (t+1Ft+2 – tFt+2) / Pt; where t+1Ft+2 = the first individual analyst forecast of t+2 earnings issued after the end of the return accumulation period; and tFt+2 = the most recent forecast of t+2 earnings issued prior to the beginning of the return accumulation period ACCt = (NOAt – NOAt-1) / NOAt-1 = the percentage change in Non-cash Net Operating Assets, defined as total operating accruals for fiscal year t. NOAt = Total operating assets – Total operating liabilities for fiscal year t, where cash and investments are defined as financial assets [Item #6 – Item #1 – Item #32 – (Item #181 – Item #34 – Item #9)]. SGt = sales growth, calculated as (Salest / Salest-1) – 1, where Sales is Item #12. ∆EFFt = the deflated change in asset efficiency, calculated as (ATt – ATt-1) / ATt, where ATt = Salest / NOAt. RNOAt = return on net operating assets for fiscal year t, calculated as operating income after depreciation (Item #178) deflated by NOAt-1. FCFt = free cash flow deflated by NOAt-1, calculated as RNOAt – ACCt. DIST_EQt = net equity distributions, calculated as (∆Item #6 – ∆Item #181 - ∆Item #32 – Item #178) deflated by NOAt-1.
DIST_Dt = net debt distributions, calculated as (∆Item #9 + ∆Item #34) deflated by NOAt-1.
24
DISTt = net distributions to capital providers, calculated as DIST_EQt + DIST_Dt.
∆CASHt = change in cash balance, calculated as ∆Item #1 deflated by NOAt-1.
25
References
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28
Table 1 Sample Selection
All Compustat firm-years from 1988 to 2006 186,928 Exclude financial firms (SIC codes 6000-6999) -32,923 Exclude firm-years missing data needed to compute cash flow and accrual earnings component variables or where NOA < 0 -56,001
Exclude firm-years without matching CRSP data needed to compute RET -29,649 Exclude firm-years without matching I/B/E/S data needed to compute FE -51,661 Subtotal 16,684 Exclude firm-years without data needed to compute FREV -7,929 Number of firm-years in final sample 8,755
*See appendix A for variable definitions.
29
Table 2 Descriptive Statistics
Panel A: Univariate Statistics (variables winsorized at +/- 1 except RET) Mean Std.Dev. 25% Median 75% SG 0.158 0.250 0.025 0.109 0.238 ∆AT -0.026 0.278 -0.109 0.008 0.102 ∆CASH 0.043 0.267 -0.017 0.003 0.057 DIST_EQ 0.102 0.308 0.040 0.109 0.194 DIST_D -0.065 0.240 -0.102 -0.002 0.027 DIST 0.037 0.394 -0.042 0.090 0.197 FCF 0.080 0.405 -0.033 0.100 0.225 ACC 0.175 0.400 -0.011 0.088 0.265 RNOAt 0.256 0.385 0.109 0.188 0.323 FE -0.009 0.059 -0.012 -0.001 0.003 A/P 0.046 0.087 0.034 0.055 0.074 F/P 0.056 0.079 0.042 0.060 0.080 FREV -0.011 0.051 -0.023 -0.004 0.004 RET 0.039 0.566 -0.239 -0.033 0.197
*See appendix A for variable definitions.
30
Table 2 Descriptive Statistics (cont’d)
Panel B: Correlation Matrix—Pearson above diagonal and Spearman below diagonal (p-values below correlations) RETt+1 FEt+1 At/Pt Ft/Pt FREVt+2 SGt ∆EFFt ∆CASHt DIST_EQt DIST_Dt DISTt FCFt ACCt RNOAt RETt+1 1 0.334 0.044 0.041 0.268 -0.029 0.051 0.003 0.062 0.041 0.082 0.076 -0.067 0.007 <.0001 <.0001 <.0001 <.0001 0.0057 <.0001 0.7371 <.0001 <.0001 <.0001 <.0001 <.0001 0.4864 FEt+1 0.165 1 0.065 -0.032 0.002 -0.013 0.080 0.058 0.038 0.065 0.079 0.100 -0.082 0.015 <.0001 <.0001 0.0021 <.0001 0.2186 <.0001 <.0001 0.0003 <.0001 <.0001 <.0001 <.0001 0.1542 At/Pt -0.060 0.390 1 0.744 0.017 0.027 0.028 0.015 0.227 0.022 0.186 0.189 0.019 0.271 <.0001 <.0001 <.0001 0.0982 0.0102 0.0074 <.0001 <.0001 0.0346 <.0001 <.0001 0.0636 <.0001 Ft/Pt -0.056 -0.131 0.763 1 0.029 -0.150 -0.031 -0.081 0.186 -0.011 0.137 0.091 -0.057 0.042 <.0001 <.0001 <.0001 0.0060 <.0001 0.0036 <.0001 <.0001 0.2867 <.0001 <.0001 <.0001 <.0001 FREVt+2 0.137 0.383 0.021 -0.021 1 -0.024 0.028 0.030 0.023 0.041 0.048 0.056 -0.037 0.012 <.0001 <.0001 0.0399 0.0480 0.0236 0.0076 0.0044 0.0313 0.0001 <.0001 <.0001 0.0004 0.2494 SGt -0.008 0.001 0.060 -0.041 -0.004 1 0.188 0.210 -0.274 -0.276 -0.382 -0.233 0.491 0.264 0.4150 0.8565 <.0001 <.0001 0.6730 <.0001 <.0001 <.0001 <.0001 <.0001 <.0001 <.0001 <.0001
∆EFFt 0.046 0.022 -0.007 -0.029 0.019 0.198 1 0.158 0.180 0.377 0.370 0.465 -0.713 -0.251 <.0001 0.0337 0.4990 0.0055 0.0714 <.0001 <.0001 <.0001 <.0001 <.0001 <.0001 <.0001 <.0001
∆CASHt -0.001 0.028 0.043 -0.001 0.009 0.159 0.241 1 -0.300 -0.106 -0.299 0.367 0.021 0.407 0.8871 0.0077 <.0001 0.8908 0.3669 <.0001 <.0001 <.0001 <.0001 <.0001 <.0001 <.0001 <.0001
DIST_EQt 0.021 0.039 0.107 0.118 0.017 -0.164 0.085 -0.148 1 0.021 0.793 0.575 -0.332 0.259 0.0493 0.0002 <.0001 <.0001 0.1067 <.0001 <.0001 <.0001 0.0408 <.0001 <.0001 <.0001 <.0001
DIST_Dt 0.043 0.018 0.007 -0.008 0.009 -0.221 0.370 -0.005 -0.029 1 0.625 0.539 -0.508 0.037 <.0001 0.0846 0.4759 0.4224 0.3626 <.0001 <.0001 0.5761 0.0060 <.0001 <.0001 <.0001 0.0004
DISTt 0.042 0.042 0.088 0.087 0.019 -0.284 0.334 -0.141 0.710 0.561 1 0.777 -0.569 0.225 <.0001 <.0001 <.0001 <.0001 0.0698 <.0001 <.0001 <.0001 <.0001 <.0001 <.0001 <.0001 <.0001 FCFt 0.040 0.059 0.114 0.084 0.025 -0.205 0.468 0.311 0.542 0.531 0.799 1 -0.541 0.488 0.0001 <.0001 <.0001 <.0001 0.0182 <.0001 <.0001 <.0001 <.0001 <.0001 <.0001 <.0001 <.0001 ACCt -0.047 -0.022 0.052 0.005 -0.020 0.507 -0.640 -0.099 -0.183 -0.512 -0.505 -0.566 1 0.469 <.0001 0.0341 <.0001 0.6388 0.0539 <.0001 <.0001 <.0001 <.0001 <.0001 <.0001 <.0001 <.0001 RNOAt -0.006 0.039 0.174 0.093 0.005 0.362 -0.176 0.220 0.381 -0.001 0.264 0.363 0.411 1 0.5410 0.0002 <.0001 <.0001 0.6314 <.0001 <.0001 <.0001 <.0001 0.8538 <.0001 <.0001 <.0001
31
32
Table 3 Mean Returns and Forecast Errors
Sorted on Earnings Component Deciles * Panel A: Deciles formed based on the cash flow variable (FCFt)
Decile FCFt FEt+1 RETt+1 1 -0.715 -0.016 0.005 2 -0.173 -0.024 0.009 3 -0.041 -0.014 0.044 4 0.026 -0.015 0.026 5 0.076 -0.010 0.023 6 0.121 -0.006 0.048 7 0.167 -0.008 0.055 8 0.228 -0.006 0.021 9 0.340 0.097 0.051
10 0.774 -0.005 0.109 Differences between 10th and 1st deciles **
0.011 (0.020)
0.104 (0.140)
Panel B: Deciles formed based on the total accruals variable (ACCt) Decile ACCt FEt+1 RETt+1
1 -0.326 -0.010 0.128 2 -0.072 -0.008 0.054 3 -0.010 -0.008 0.062 4 0.028 -0.012 0.035 5 0.070 -0.011 0.028 6 0.118 -0.009 0.034 7 0.180 -0.012 0.029 8 0.270 -0.013 0.019 9 0.440 -0.015 0.009 10 1.058 -0.013 -0.004
Differences between 10th and 1st deciles **
-0.003 (0.725)
-0.132 (0.055)
* See appendix A for variable definitions. ** Two-tailed p-values are in the parentheses.
33
Table 3 (continued)
Panel C: Deciles formed based on the sales growth component of total accruals (SGt)
Decile SGt FEt+1 RETt+1 1 -0.185 -0.015 0.034 2 -0.020 -0.014 0.075 3 0.025 -0.008 0.022 4 0.059 -0.008 0.055 5 0.092 -0.009 0.016 6 0.130 -0.009 0.030 7 0.176 -0.013 0.010 8 0.242 -0.011 0.060 9 0.358 -0.011 0.056
10 0.701 -0.012 0.032 Differences between 1st and
10th deciles -0.003 (0.393)
0.002 (0.978)
Panel D: Deciles formed based on the efficiency change component of total accruals (ΔEFFt) Decile ΔEFFt FEt+1 RETt+1
1 -0.621 -0.014 -0.018 2 -0.225 -0.018 -0.005 3 -0.115 -0.112 0.044 4 -0.054 -0.010 0.028 5 -0.012 -0.010 0.035 6 0.024 -0.010 0.036 7 0.059 -0.007 0.038 8 0.104 -0.007 0.064 9 0.174 -0.013 0.065 10 0.398 -0.010 0.106
Differences between 10th and 1st deciles
0.004 (0.443)
0.124 (0.049)
34
Table 3 (continued)
Panel E: Deciles formed based on the change in cash balance component of free cash flows (ΔCASHt)
Decile ΔCASHt FEt+1 RETt+1 1 -0.365 -0.016 0.109 2 -0.065 -0.013 0.038 3 -0.019 -0.011 0.034 4 -0.004 -0.012 -0.007 5 0.001 -0.009 -0.012 6 0.009 -0.010 0.027 7 0.024 -0.009 0.019 8 0.061 -0.010 0.033 9 0.164 -0.011 0.056 10 0.629 -0.008 0.097
Differences between 10th and 1st deciles 0.008
(0.035) -0.012 (0.823)
Panel F: Deciles formed based on the net distributions to stockholder component of free cash flows (DIST_EQt)
Decile DIST_EQt FEt+1 RETt+1 1 -0.529 -0.018 0.025 2 -0.054 -0.016 0.014 3 0.037 -0.020 0.047 4 0.072 -0.014 0.037 5 0.097 -0.011 0.023 6 0.009 -0.005 0.048 7 0.152 -0.007 0.044 8 0.197 -0.006 0.041 9 0.287 -0.008 0.052 10 0.643 -0.005 0.059
Differences between 10th and 1st deciles
0.013 (0.028)
0.034 (0.729)
Panel G: Deciles formed based on the net distributions to debtholder component of free cash flows (DIST_Dt)
DIST_Dt FEt+1 RETt+1 1 -0.610 -0.013 -0.036 2 -0.208 -0.019 0.023 3 -0.107 -0.016 -0.006 4 -0.052 -0.008 0.034 5 -0.018 -0.009 0.043 6 -0.001 -0.009 0.101 7 -0.044 -0.010 0.055 8 0.028 -0.007 0.078 9 0.067 -0.008 0.058
10 0.241 -0.011 0.040 Differences between 10th and 1st deciles
0.002 (0.772)
0.076 (0.018)
35
Table 4 Regressions of Future Earning Performance on Accrual Components and Cash Flow
Components of Current Earnings Performance (8,755 observations spanning the years 1988-2006)
Panel A: Regression analyzing the persistence of the free cash flow and total operating accruals Model (5): RNOAt+1 = θ0 + θ1 FCFt + θ2 ACCt + ηt+1 Intercept FCF ACC Adj. R2
Coefficient 0.115 0.618 0.420 0.336 (t-statistic) (11.83)a (14.94)a (12.71)a
Panel B: Regression analyzing the persistence of accrual components and cash flow components Model (6): RNOAt+1 = λ0 +λ 1∆CASHt + λ2DIST_EQt +λ 3DIST_Dt + λ4SGt +λ θ5ΔEFFt + λ6(SGt * ΔEFFt) + ξt+1 Intercept ∆CASH DIST_EQ DIST_D SG ΔEFF SGt * ΔEFF Adj. R2 Coefficient 0.086 0.647 0.658 0.513 0.532 -0.336 -0.281 0.380 (t-statistic) (7.11)a (14.06)a (13.25)a (9.25) a (11.40)a (-7.23)a (-3.92)a
a indicates two tailed P value associated with t-stats is less than 0.01; b indicates two tailed P value associated with t-stats is less than 0.05; c indicates two tailed P value associated with t-stats is less than 0.10. The Fama-MacBeth procedure is employed to run cross-sectional regressions (associated t-statistics in parentheses).
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Table 5 The Behavior of Stock Returns Following Publication of Detailed Cash and Accrual
Earnings Information (8,755 observations spanning the years 1988-2006)
Panel A: OLS Regression for Total Operating Accruals Model (7): RETt+1 = α0 + α 1 FCFt + α 2 ACCt + ut+1 Intercept FCF ACC Adj. R2
Coefficient 0.047 0.018 -0.062 0.009 (t-statistic) (1.97)c (0.69) (-2.42)b
Panel B: OLS Regression for Growth and Efficiency Decomposition of Accruals RETt+1 = β0 + β1 FCFt + β2 SGt + β3ΔEFFt + β4[(SGt)*(ΔEFFt)] + ωt+1 Our Results (8,755 firm-years spanning 1988-2006) Intercept FCF SG ΔEFF SG * ΔEFF Adj. R2
Coefficient 0.044 0.005 -0.015 0.121 0.023 0.015 (t-statistic) (1.87)c (0.19) (-0.30) (3.80)a (0.37)
Panel C: OLS Regression of subsequent years returns on accrual and cash flow components RETt+1 = κ0 + κ1 ∆CASHt + κ2 DIST_EQt + κ3 DIST_Dt + κ4 ACCt + ςt+1
Intercept ΔCash DIST_EQ DIST_D ACC Adj. R2 Coefficient 0.049 0.008 0.003 0.064 -0.051 0.012 (t-statistic) (1.85)c (0.24) (0.08) (2.33)b (-2.03)c
Panel D: OLS Regression of subsequent years returns on accrual components and cash flow components Model (8): RETt+1 = γ0 + γ1∆CASHt + γ2 DIST_EQt + γ3DIST_Dt + γ4 SGt + γ5ΔEFFt + γ6(SGt * ΔEFFt) + et+1 Intercept ∆CASH DIST_EQ DIST_D SG ΔEFF SGt * ΔEFF Adj. R2 Coefficient 0.046 -0.014 0.0002 0.057 0.0006 0.110 -0.007 0.018 (t-statistic) (1.77)c (-0.41) (0.01) (2.01)c (0.01) (3.41)a (-0.12)
a indicates two tailed P value associated with t-stats is less than 0.01; b indicates two tailed P value associated with t-stats is less than 0.05; c indicates two tailed P value associated with t-stats is less than 0.10. The Fama-MacBeth procedure is employed to run cross-sectional regressions (associated t-statistics in parentheses).
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Table 6 The Behavior of Analysts’ Earnings Forecasts
Following Publication of Detailed Cash and Accrual Earnings Information (8,755 firm-years spanning 1988-2006)
Panel A: Summary model regressing subsequent forecast errors on cash and accrual earnings Model (9): FEt+1 =β0 + β1FCFt + β2ACCt + εt+1
Intercept FCF ACC Adj. R2 Coefficient -0.013 0.0130 0.005 0.006 (t-statistic) (-5.18)a (3.91)a (1.91)c
Panel B: Components model regressing subsequent forecast errors on cash and accrual earnings components FEt+1 = δ0 + δ1FCFt + δ2SGt + δ3ΔEFFt + δ4[(SGt)*(ΔEFFt)] + ωt+1
Intercept FCF ∆SG ΔEFF SG * ΔEFF Adj. R2 Coefficient -0.014 0.014 0.009 -0.008 0.006 0.010 (t-statistic) (-5.57)a (3.97)a (2.07)c (-1.59) (0.76)
Panel C: OLS Regression for Growth, Efficiency, ∆CASH, DIST_EQ, and DIST_D Model (10) : FEt+1 = δ0 + δ1∆CASHt + δ2 DIST_EQt + δ3DIST_Dt + δ4
*SGt + δ5ΔEFFt + δ6 [(SGt)*(ΔEFFt)] + ωt+1 Intercept ∆CASH DIST_EQ DIST_D SG ΔEFF SG *ΔEFF Adj. R2 Coefficient -0.014 0.012 0.017 0.010 0.007 -0.006 0.010 0.012 (t-statistic) (-5.03)a (4.02)a (2.84)b (2.95)a (1.74)c (-1.25) (1.39)
a indicates two tailed P value associated with t-stats is less than 0.01; b indicates two tailed P value associated with t-stats is less than 0.05; c indicates two tailed P value associated with t-stats is less than 0.10. The Fama-MacBeth procedure is employed to run cross-sectional regressions (associated t-statistics in parentheses).
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Table 7 Analyst Forecasting Behavior as an Explanation for Market Inefficiency with Respect to
Information in Cash and Accrual Components of earnings (8,755 firm-year observations from 1988 to 2006)
Panel A: OLS Regression for Accruals Model (7): RETt+1 = α0 + α 1FCFt + α 2ACCt + ut+1 Model (11) : RETt+1 = ρ0 + ρ1FCFt + ρ2ACCt + ρ3FEt+1 + ρ4FREVt+2+ et+1
Intercept FCF ACC FE FREV Adj. R2
Model (7) Coefficient 0.047 0.018 -0.062 0.009 (t-statistic) (1.97)c (0.69) (-2.42)b
Model (11) Coefficient 0.079 -0.004 -0.060 1.709 1.225 0.083 (t-statistic) (3.28)a (-0.16) (-2.34)b (6.00)a (6.14)a
Panel B: OLS Regression for Growth, Efficiency, ∆CASH, DIST_EQ, and DIST_D Model (8): RETt+1 = γ0 + γ1∆CASHt + γ2 DIST_EQt + γ3DIST_Dt + γ4 SGt + γ5ΔEFFt + γ6(SGt * ΔEFFt) + et+1 Model (12): RETt+1 =φ0 +φ1∆CASHt + φ2 DIST_EQt + φ3DIST_Dt+ φ4 SGt +φ5ΔEFFt + φ6(SGt)*(ΔEFFt) + φ7FEt+1 + φ8FREVt+2 + μt+1 Intercept ∆CASH DIST_EQ DIST_D SG ΔEFF SGt * EFF FE FREV Adj. R2
Model (8) Coefficient 0.046 -0.014 0.0002 0.057 0.0006 0.110 -0.007 0.018 (t-statistic) (1.77)c (-0.41) (0.01) (2.01)c (0.01) (3.41)a (-0.12)
Model (12) Coefficient 0.081 -0.035 -0.027 0.037 -0.005 0.104 -0.015 1.727 1.213 0.092 (t-stat.) (3.06)a (-0.92) (-0.71) (1.24) (-0.11) (3.43)a (-0.28) (6.02)a (6.10)a
a indicates two tailed P value associated with t-stats is less than 0.01; b indicates two tailed P value associated with t-stats is less than 0.05; c indicates two tailed P value associated with t-stats is less than 0.10. The Fama-MacBeth procedure is employed to run cross-sectional regressions (associated t-statistics in parentheses).