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Quantitative Easing and Equity Responses:
Insights from the MPC’s Framework
Georgios Chortareas*, Menelaos Karanasos**, and Emmanouil Noikokyris***
ABSTRACT
This paper explores the effects of Monetary Policy Committee's (MPC) asset purchase
announcements and communications on the UK stock market for the period 2009-2014. We
use intraday aggregate stock market data and an event study framework to assess the equities’
reaction, both their level and volatility, to survey-based measures for monetary policy stance
over a variety of time frames both preceding and following the MPC announcements. Our
results show that UK monetary policy shocks exhibit a significant impact on domestic equity
returns and volatilities. The strength of this impact hinges on the BoE’s information
dissemination through inflation reports and the MPC's voting records. Moreover, there is
evidence of news spillage prior to the announcement time.
JEL Codes: G14, E44, E52.
Keywords: Monetary Policy Committee (MPC), Intra-day data, equities response, monetary
policy shocks, equities volatility.
* Georgios Chortareas, School of Business and Management, King's College London, Franklin-Wilkins
Building, 150 Stamford Str., London SE1 9NH, UK, Email address: [email protected]
** (Corresponding author) Menelaos Karanasos Brunel University Business School, Brunel
University, Middlesex UB3 3PH, UK Email address: [email protected]
*** and Emmanouil Noikokyris Kingston Business School, Kingston University London, Kingston Hill,
Kingston upon Thames KT2 7LB, UK, Email address: [email protected]
1
1. Introduction.
The European Central Bank (ECB) initiated its quantitative easing (QE thereafter) program in
March 2015, and by the end of the same year decided to further expand the duration of the
program beyond September 2016, which was initially announced. Other central banks adopted
QE policies since late 2008 (US) and 2009 (UK) and an extensive literature analyzes their
effectiveness, with different conclusions about its effects on the real economy and financial
markets. In this paper, we examine the UK experience focusing on the reaction of stock market
returns and their volatility to asset purchases from the Bank of England’s (BoE thereafter)
Asset Purchase Facility (APF thereafter). Moreover, along with the introduction of QE by the
ECB its president has emphasized the unanimity of decisions in his introductory statement to
the press conference following the policy announcements. While the ECB's communication
framework is considered effective (Ehrmann and Fratzscher, 2007), the corresponding
framework of the BoE allows for important pieces of information to be disseminated on a
regular and systematic basis through the paraphernalia of inflation targeting. From this
perspective, the experience of UK's monetary policy implementation may constitute an
important reference point for the euro zone which takes its first steps in the implementation of
QE easing polices.
We consider the period from the onset of QE in September 2009 until March 2014,
during which the base policy rate of the BoE has been stable at the effective lower bound of
0.5%, and monetary policy is conducted through the APF's purchase of assets worth £375
billion funded by the expansion of the BoE’s balance sheet. While the impact of QE on
economic output and other macroeconomic variables can be long-lagged, the potential effect
on financial assets can be direct and more pronounced as the last respond faster to news. We
try to advance our understanding of how QE affects financial markets by considering the
impact of QE surprises not only on stock returns but on volatility as well. In addition, we
2
consider how the BoE's communication policy may affect the impact of QE policies on stock
returns.
In particular, the present paper pursues the following contributions. First, we examine
the implications of the BoE’s MPC (Monetary Policy Committee) framework for the
relationship between QE and stock returns focusing on the publication of inflation reports and
the MPC meetings minutes. To our knowledge this is the first attempt to analyze the role of
information releases (inflation forecasts and minutes) by the central bank in the context of QE
policies. Second, we examine the impact of BoE’s QE on equity returns volatility, as well as
the influence of the MPC framework on the magnitude of this relationship. To our knowledge
there is no other similar study for the UK, while scant evidence has been produced for the US.
We consider both implied and, several different types of, realized volatility. Third, we
investigate whether a significant pre-announcement drift exists in the UK as it has been
reported for the US (Lucca and Moench, 2015). Again this is the first attempt to identify the
presence of a drift in equity prices during the hours leading up to the BoE's MPC
announcements. Fourth, using survey-based measures of unexpected QE announcements and
intraday equity returns, we find that QE surprises have a minuscule impact on UK equities.
During the first hour following the MPC announcement there is no impact. When we consider
the wider sample, extending from 10 minutes before the announcements up to the end of the
announcement day, we find that smaller than expected asset purchases reduce equity prices.
A voluminous literature on the relationship between QE policies and asset prices has
evolved since the outbreak of the recent financial crisis and the subsequent adoption of QE
policies by many central banks around the globe. The bulk of evidence comes from the US and
employs event study frameworks to examine the reaction of financial assets' prices to central
bank QE announcements. This stream of literature typically gauges the efficacy of the Federal
Reserve’s QE as the cumulative change in the price of a financial asset in a short window
3
bracketing those QE related announcements (see e.g., Gagnon et al., 2011; D’Amico and King,
2013; Krishnamurthy and Vissing-Jorgensen, 2011; Meaning and Zhu, 2011; Neely, 2015;
Swanson, 2011), and its results point out to the effectiveness of QE in lowering longer-term
rates. Evidence also exists on the Fed’s QE programs impact on a wider array of financial
assets. Neely (2015), for instance, finds that Fed’s QE announcements lower global long-term
interest rates as well as the price of the dollar, while Meaning and Zhu (2011) find that large
scale asset purchases by the Fed increase equity prices and lower the level of implied volatility
in the market.
While the majority of the evidence concerns the impact of the asset purchases
conducted by the Fed, an active interest exists on the financial market implications of the BoE’s
QE program. In the UK, much of the extant literature examines the impact of QE
announcements on financial markets using event study frameworks, and the results from these
studies report significant reductions in government gilt yields in the wake of QE
announcements (e.g., Joyce et al., 2011; Breedon et al., 2012; Joyce et al., 2012; Joyce and
Tong, 2012). In terms of the equities reaction, however, the evidence produced from the early
days of the BoE’s QE program implementation is inconclusive. Breedon et al., (2012) suggest
that there is not a differential reaction of equity prices as a consequence of the bond purchase
operations during BoE’s first QE programme in 2009-2010. The results of Joyce et al. (2011),
however, who consider the same period show small and positive responses of equities which,
nevertheless are not uniform across all 6 QE announcements in the sample. While Breedon et
al., (2012) investigate the equities' reactions on the days that asset purchases were conducted,
Joyce et al. (2011) consider the days of asset purchases' announcements. In this paper we
identify the equity market implications of the BoE’s announcements about the APF asset
purchases by capturing the equities responses within a short window bracketing the QE
announcements. We assume that the forward-looking nature of the equity markets incorporates
4
the QE news on the announcement day and not on the day the asset purchases are conducted,
as is typically the case in the related literature (see e.g., Joyce et al., 2011 and Wright, 2012).
Nevertheless, our study is most closely related to those studies associating the size of equities
reaction with the amount of QE news released from each central bank announcement. The
unexpected element of QE announcements is calculated in a variety of ways using market data
(e.g., Gospodinov and Jamali, 2012; Rogers et al., 2014; Wright, 2012), economists’ surveys
(e.g., Cahill et al., 2013; Joyce et al., 2011; McLaren et al., 2014) and newspaper articles (e.g.,
Rosa, 2012).
The existing evidence for the UK shows small, if any, equity reactions to QE news from
MPC meetings. Rosa (2012) finds that until June 2011 equity returns in the first 25 minutes
following an MPC announcement are not associated with QE news from the MPC meeting.
Rogers et al. (2014) using data until 2014, find a positive reaction of equities in the first 15
minutes of the announcement to easing market-based monetary policy shocks which, however,
is smaller than that reported for the US. Both studies rely only on very short intraday windows
to gauge the equities reaction, and they do not examine how the BoE’s communication
framework might influence market expectations regarding MPC meeting announcements.
A key focus of this paper is to provide a characterization of the QE effects on asset
prices volatility, again by taking into account not only the policy announcements but also the
information content of the inflation reports and of the published MPC minutes. A considerable
amount of research on the impact of monetary policy on the intraday and daily asset prices
volatility has been produced mostly before the crisis and the implementation of QE policies.
Using daily data in an event study framework Gospodinov and Jamali (2012) find that both
historical and implied volatility of US equity returns respond significantly to monetary policy
shocks. In addition, monetary policy shocks emerge as a significant determinant of other
financial asset’s intraday realized volatility, including exchange rates and bond yields
5
(Andersson, 2010; Chuliá et al., 2010). Jubinski and Tomljanovich (2013) also find that
realized volatility is sensitive to the publication of FOMC meetings minutes. Nevertheless,
hardly one can find analyses of how stock market volatility responds to QE announcements.
The results of the present study extend the existing literature on the financial market
effects of QE by showing that the time-dimension over which reactions are measured, as well
as the communication framework of the BoE’s MPC determine the strength of the transmission.
We measure the association of the survey-based proxies for the unexpected element of BoE’s
QE announcements with intraday equity returns, both before and after the MPC meeting
announcements, as well as with reference to the publication of the inflation report and of the
voting record of the MPC members. Moreover, we offer a comprehensive study on the QE
effects on the volatility of returns using both implied volatility and a wide array of realized
volatility measures calculated over different daily and intraday periods.
In Section 2 we consider the effects of QE surprises and the implications of the MPC
framework for their transmission. Section 3 shifts focus to the analysis of stock market implied
and realized volatility in response to MPC's QE announcements, and finally Section 4
concludes.
2. Quantitative Easing and the Stock Market
2.1 Quantitative Easing and Equity returns.
In this section, we consider the effects of MPC meeting announcements on the UK equity
returns during the QE period spanning from 2009 to early 2014. Our empirical strategy relies
on an event study framework that captures the equities’ reaction to the unexpected element of
MPC announcements in a short window bracketing the announcement. This type of event study
6
methodology is the workhorse model for analyzing the impact of monetary policy on stock
returns both before the crisis and the introduction of quantitative easing (e.g., Bernanke and
Kuttner, 2005; Ehrmann and Fratzscher, 2004), and afterwards (Glick and Leduc, 2012; Joyce
et. al., 2011; Rogers et. al., 2014; Wright, 2012). Some aspects of this approach have been
particularly challenging, such as the choice of a proxy for the unexpected element of the MPC’s
announcement and the length of the window over which to measure the response (Gürkaynak
and Wright, 2013).
-Figure 1 here-
Fig. 1 shows the average cumulative stock market returns on the days of MPC
announcements in relation to equity returns when there is no MPC announcement. Since all
MPC announcements take place on Thursdays,1 when considering the non-MPC meeting days
we take stock returns on all Thursdays when there is no MPC announcement in order to avoid
any day of the week effect. Although the 5-minute average cumulative returns on the FTSE-
100 index on the 55 MPC announcements are indicative of an upward trend in stock prices on
these days (especially in the hours following the announcement), by the end of the day the
stock prices usually drop to their initial level. This pattern is in contrast to the cumulative mean
returns on all other Thursdays, excluding those coinciding with MPC announcements, which
show on average zero or slightly negative equity returns. The difference between the
cumulative mean returns on MPC and non-MPC days, however, is not statistically significant,
and all pointwise means of cumulative returns are not statistically different from zero at the
95% level of significance.
Thus, a casual inspection of the descriptive statistics is not supportive of a significant
equity response to QE news from MPC announcements. The increase in equity prices during
1 The only MPC announcement which did not take place on a Thursday is that of Monday, May 10th, 2010 because
of the general elections.
7
the hours leading up to the MPC announcement, however, points to the possibility of a pre-
announcement drift similar to that reported in the US by Lucca and Moench (2015). Moreover,
the significant variance of stock prices in the hours following the announcement is indicative
of a wider window during which the complete pass-through of the announcement materializes.
The effects of Quantitative Easing Surprises
The BoE's announcements have been subjected to intense scrutiny both during the period of
conventional monetary policy and during the recent years when unconventional practices have
been adopted. Moreover, under inflation targeting the BoE's monetary policy conduct is
characterized by increased transparency. Therefore, one would expect that the MPC's
announcements are to some extent anticipated by the market. Given that equity markets do not
react to anticipated pieces of information, disentangling stock market's reaction to MPC
meetings requires the identification of the unexpected element of MPC’s QE announcements.
To define the QE surprises, we use the difference between the actual amount of asset purchases
announced by the BoE and that expected by the market before the announcement, which is
derived as the average of the forecasts provided by economists taking part in Bloomberg’s
survey. Bloomberg surveys have also been used in previous studies to infer market expectations
about the BoE’s monetary policy decisions before the commencement of the QE period (e.g.,
Melvin et. al., 2010).
-Figure 2 here-
Although the economists’ estimates in this survey are produced about a week before
the MPC meeting, Fig. 2 shows that the size of the BoE’s APF purchases is to a great extent
anticipated by the market. Specifically, at 36 out of the 55 MPC meetings taking place during
the period under examination Bloomberg economists’ forecasts match the BoE’s
announcements, while for the rest of the announcements the divergence has been less than £10
8
billion and the market in all cases was expecting higher than realized asset purchases (the
surprises are of negative sign). The only exception is the announcement on October 6th, 2011
when asset purchases were £56.25 billion greater than that expected, resulting to a large
surprise with positive sign.
The Event Window
Another contentious aspect of the event study framework is the duration of the event window.
Recent papers examine the effects of unconventional monetary policy by capturing the equities'
response to quantitative easing announcements over a short intraday window surrounding the
announcement (e.g., Rogers et al., 201; Joyce and Tong, 2012). The idea of a narrow event
window has the appealing property that the reaction estimates are not contaminated by other
news arriving on the same day and influencing equities. A very narrow window in the context
of an event study, however, might also produce misleading results. There exists, for instance,
the possibility that markets might overreact to some announcements (Thornton, 2013).
Furthermore, the market might require some additional time to fully price unconventional
monetary policy news, because of the novelty of this method of monetary policy conduct in the
UK during a period of high turbulence and disruptions in the financial markets (Gagnon et. al.,
2011; Joyce et. al., 2011; Meaning and Zhu, 2011; Neely, 2015). In this study, we capture the
equities' reaction using two intraday windows. Both windows start at 11:50am, which is 10
minutes before the announcement, but the narrower window finishes 1-hour after the MPC
announcement at 1pm, while the wider one spans up to the closing of the trading day.
The Baseline Model
9
We measure the impact of QE news on domestic equities using the following empirical
specification:
, (1)
where rt stands for the FTSE-100 index returns calculated over the two alternative event
windows described above, and St stands for the unexpected element of the MPC’s quantitative
easing announcement on the 55 announcement days t of MPC meetings that we are considering
in our study. The coefficient estimate βMP captures equities’ reaction to unexpected asset
purchases by the Bank. We start our estimations from September 2009, when the Bloomberg
survey data have become available, and we consider the period until March 2014. We report
our results using robust regression M-estimators in order to control, for the unduly influence
of outliers on our results (see also Rogers et. al., 2014),
-Table 1 here-
The results from the estimation of Eq. (1), reported in Table 1, show that the size of
equities’ reaction to Bank’s QE news hinges on the length of the event window. While during
the first hour after the announcement QE surprises do not exert an impact on equity prices,
when the event window is up to the end of the day the reaction estimate is positive and
statistically significant. Although the reaction estimate is of minuscule size, it suggests that
smaller than expected asset purchases reduce equity prices. In particular, if the BoE’s actual
asset purchases are smaller by £1 billion from what expected by the economists participating
in Bloomberg’s survey, equities drop by 0.03%.
2.2 The MPC Framework and its Implications
tt
MP
t Sar
10
To formally assess the role of the MPC framework, and in particular of the inflation report
release and of the MPC meetings minutes publications, we employ an empirical specification
consistent with that used by Chortareas and Noikokyris (2014), and we consider the specific
effects of news about asset purchases on the first, second, and third MPC meeting following
the release of the inflation report. Moreover, we investigate the marginal impact of QE news
on those MPC meetings announcements immediately following news about unanimity in the
previous MPC meeting. Specifically, we estimate the following regression:
, (2)
where I1 , I
2 and I3 are 0-1 dummy variables taking the value of 1 on the 19 first, 18 second and
18 third MPC meetings following the release of the inflation report respectively, and zero
otherwise. IUNA is a 0-1 dummy variable taking the value of 1 on the 27 MPC meeting days
directly following MPC meetings minutes releases indicating unanimity in the decision of the
previous MPC meeting regarding the size of BoE’s APF purchases. Finally, IAP is a 0-1 dummy
variable taking the value of 1 on the 4 MPC meetings when there was a change in the size of
the program.
The results from the estimation of Eq. (2), reported in Table 1, show that during the
first hour after the MPC announcement equities react to those MPC announcements which
directly follow or precede the two elements of the MPC framework attracting most of the public
attention; the inflation report release and a unanimous MPC decision. In particular, we find that
on MPC meetings taking place a week before the inflation report release smaller than expected
asset purchases are perceived as good news by the stock market increasing stock prices. To the
extent that the announcement reveals MPC members’ private view on future economic
conditions, smaller than expected asset purchases might be perceived as a possibility of better
tt
AP
t
UNA
tttt SISISISISIar 54
3
3
2
2
1
1
11
than expected news from the forthcoming inflation report release, constituting essentially this
MPC meeting a forerunner of the inflation report.
On MPC meeting days following news of a unanimous decision in the previous
committee meeting, the positive reaction estimate suggests that stock prices drop following
news about smaller than expected asset purchases. This finding of a more pronounced
transmission on these occasions is consistent with that observed during the conventional
monetary policy conduct period from 1994 to 2008 (Chortareas and Noikokyris, 2014).
Considering the individualistic nature of the MPC’s decision-making process (Blinder and
Wyplosz, 2004), the dissenting votes and the discussions explaining them, constitute an integral
part of the information set available to investors. The absence of opposing views, can be
interpreted as a limitation to the information available to investors about future monetary
policy, which in turn can lead to overreactions. The lack of dissenting votes, however, can also
be perceived as a strong signal about MPC members’ intentions increasing the informational
content of the MPC meetings decisions. If the last is the case, we should expect investors to
uniformly adjust their pricing discovery process reducing equity returns volatility. If the lack
of dissenting votes, however, creates uncertainty over the way MPC members view current and
future economic activity, this will raise volatility.
When, however, the wider event window is considered, we find that UK equities
respond only to QE surprises from the second MPC meetings following inflation report
releases. The absence of a statistically significant relationship between QE surprises and
equities on the first and third MPC meetings following the inflation report release illustrates
the informational dominance of the inflation report on the market participants’ expectations
about the future monetary policy stance and economic output. The equity market reacts to QE
news from MPC meetings only when there has not been an inflation report during the past
month or only when it is not awaiting an inflation report within the following week. In the first
12
hour we report a reaction to news attracting media attention, such as unanimity in MPC
decisions or imminent inflation report releases, while when there is enough time to process the
announcement the market seems to respond, in a manner consistent with theory, to the
economic news deriving from the announcement. The finding that the BoE’s MPC framework
weights differently in investors’ price discovery process, depending on the event window
employed, is indicative of the difficulties that stock market participants face when pricing the
QE news.
2.3 The Pre-Announcement Drift
In this section we investigate whether equity returns exhibit systematic large values in
the hours leading up to the MPC announcement. In Fig. 1, we show that, although statistically
insignificant, equities display an upward drift in the hours before the announcement. To
formally examine the presence of a pre-announcement drift, we investigate whether returns are
systematically larger during the time leading up to the MPC announcement using the following
empirical specification of Lucca and Moench (2015):
t
MPCpre
tt Iar . (3)
In Eq. (3) rt stands for the returns on the FTSE-100 Index from the start of the trading
day until 11:55am, while MPCpreI is a dummy variable taking the value of 1 for the 55 pre-
announcement windows which are followed directly by MPC announcements and zero
otherwise. To ensure that our results are not driven by the choice of the size of the pre-
announcement window, we also employ a wider window over which we measure stock returns
which starts at 12 noon on the previous to the announcement day. We report the results from
the estimation of Eq. (3) in Table 2, and, similarly to Lucca and Moench (2015), they are not
13
indicative of significant pre-announcement effects. In particular, coefficient estimates β for the
dummy variables for both pre-announcement windows are statistically insignificant (columns
(1) and (2) in Table 2), and they remain so even after we trim our sample from the top and
bottom 1% stock returns (columns (3) and (4) in Table 2).
-Table 2 here-
To analyze the pattern of the pre-MPC stock returns more carefully, we also examine
whether they are associated with economic activity, stock market uncertainty, and ex-post QE
surprises following the original specification of Lucca and Moench (2015). To start with, we
explore the extent to which pre-MPC returns are associated with the annual growth rate of the
industrial production index and the consumer price index. We obtain the growth rate of both
variables using data from OECD’s real time and revisions database.2 The results from this
regression, presented in column (5) of Table 2, do not show strong association with the
economic activity variables. The pre-MPC equity returns, however, exhibit strong positive
association with stock market uncertainty, measured by the closing level of the FTSE IVI Index
two days before the announcement, and with the ex-post monetary policy surprises as shown
in columns (6) and (7) of Table 2 respectively. The existence of a statistically significant
relationship between pre-MPC returns and ex-post QE surprises is an indication of news
spillage, and might explain the numerically small reaction estimate of equities to QE news that
we have shown above when this relationship is considered for samples starting 10 minutes
before the announcement.
3. The MPC Announcements and Stock Market Volatility
Implied versus Realized Volatility
2 All variables enter the regressions demeaned and normalized by their standard deviation.
14
In this section we investigate the effects of the MPC announcements on the UK stock market
volatility. In order to gauge the response of the volatility to the unexpected element of the
Bank’s asset purchases announcements, we employ the event study framework from the
previous section. We consider several measures of daily and intra-day volatility, both historical
(realized) and implied, to provide a complete characterization of the impact of the 55 MPC
announcements considered in this study.
We begin by examining the association of the unexpected element of BoE’s QE
announcements with UK stock market’s realized and implied volatility. The measure of implied
volatility (IV) we use is the FTSE-100 implied volatility index. This index measures the
interpolated 30-day expected volatility, and is calculated using the prices of out-of-money
traded options. Data for the realized volatility of the FTSE-100 Index (RV) are taken from
Oxford-Man Institute’s “realized library” (Gerd et al., 2009). The measures for realized
variance are produced daily using high frequency data from that day only. We use the event
study framework employed in the previous section to obtain the reaction of these two measures
of volatility on the QE surprises from MPC meetings. In particular, we estimate the following
regression which captures the specific impact of QE surprises from the first, second, and third
MPC meeting following the release of the inflation report on equity volatilities, as well the
marginal reaction of the volatility to MPC announcements following news about a unanimous
decision and about a change in the size of BoE’s APF:
. (4)
ΔVt now stands for the first difference of implied (ΔIVt) or realized volatility (ΔRVt).
-Table 3 here-
tt
AP
t
UNA
tttt SISISISISIaV 54
3
3
2
2
1
1
15
We report the results from the M-estimation of the regression in Eq. (4) for the response
of implied volatility to QE surprises in column (1) of Table 3. As the results reveal QE surprises
do not influence the level of implied volatility in the market. The statistically insignificant
reaction of the daily changes in volatility to QE surprises suggests that expected volatility in
the UK stock market is not influenced by news regarding asset purchases emerging from MPC
meeting announcements. The statistically significant and of negative sign estimate for the
intercept, however, suggests that markets revise downwards their expectations regarding the
volatility over the next 30 days in response to the announcement. Expectations about lower
volatility could be attributed to the coordination of investors’ beliefs in the wake of the MPC
meeting announcement. For instance, Ehrmann and Sondermann (2012) find that certain
macroeconomic announcements, as well as the Banks’ inflation report release, reduce UK stock
market's conditional volatility when controlling for the news included in them.
Our results regarding the reaction of realized volatility to QE surprises on MPC meeting
days are reported in column (2) of Table 3. Contrary to implied volatility that reduces in the
wake of an MPC meeting announcement, our results show that the level of the realized variance
increases, and the difference between these two intercept estimates is statistically significant
as shown in column (3) of Table 3. Moreover, when we analyze the association between QE
news from MPC announcements and realized volatility, our results show that smaller than
expected asset purchases reduce daily realized volatility on the second MPC meeting days
following inflation report releases, unless this announcement increases the size of BoE’s APF,
when in this case realized volatility increases. These results suggest that news about smaller
than expected asset purchases on MPC meetings when no changes in the size of the amount of
asset purchases have taken place reduces not only equity prices (see Table 2), but also reduces
the realized volatility. The equity market appears not only to incorporate the news regarding
16
BoE’s asset purchases in a manner consistent with theoretical priors, but also the BoE achieves
to do so by coordinating market expectations.
Robustness Checks
To investigate further whether the reported reaction of realized volatility hinges on the measure
employed and, in particular, on whether stock market data only from the MPC meeting
announcement day are employed to gauge that day’s realized volatility, we also use two
alternative proxies for realized volatility that have been used in previous research. The first one
is the forward looking measure for (annualized) realized variance of Gospodinov et al. (2006)
which is also used in Gospodinov and Jamali (2012). Based on this specification the stock
market’s realized volatility on day t (RVG) is constructed using the 22 days-ahead squared stock
returns as follows:
, (5)
where τ stands for the days-ahead of day t and takes the value of 22. The second measure for
realized volatility is that used by Chuliá et al. (2010) and is constructed as follows:
252),
(
2
u
k
C
t ktRRV , (6)
where Rk is the 5-minute returns on the FTSE-100 Index on day t, and u measures all 5-minutes
intervals on trading day t. The first 5-minute interval following the MPC announcement is
excluded from the calculation of the realized volatility on MPC announcement days.
The results from the estimation of Eq. (4) when the dependent variable is ΔRVG and
ΔRVC are reported in columns (4) and (5) of Table 3 respectively. Our results show that the
2521
1
2
,
ti
i
G
t rRV
17
realized volatility, when measured using daily returns from 22 days ahead, does not respond to
QE surprises, as all reaction estimates are statistically insignificant. However, when the
realized volatility of stock returns on MPC announcement days is calculated from Eq. (6), using
intraday data from that day only, our results are similar to those obtained when we use the
realized volatility from Gerd et al. (2009) database. The absence of a significant response when
the measure is constructed excluding data from the MPC announcement day suggests that the
MPC announcements’ impact is traced only on the announcement day.
-Table 4 here-
Intraday Volatility
Finally, in this section we also use the same regression of Eq. (2) in order to study the impact
of MPC announcements on intraday measures of UK equity returns volatility. We use two
measures of intraday volatility in order to gauge the impact of the MPC announcement on UK
equity volatility in the hour bracketing the announcement. The first one is obtained from Eq.
(6), but now instead of calculating the daily realized volatility, we calculate equities’ realized
volatility for the period starting 10 minutes before the announcement up until 1 hour after the
announcement.
The second measure is the change in volatility ratios (ΔVolR) for equity returns used by
Andersson (2010). This measure of volatility presents the difference between the volatility ratio
in the hour following the MPC announcement and the volatility ratio for the 30 minutes before
the announcement. The volatility ratio for returns on FTSE-100 index is calculated using the
5-minute returns on the index, and is measured as the ratio of stock returns volatility on day t
of an MPC announcement for a specific period of time (either the 30 minutes before the
18
announcement or the 1 hour following the announcement) to stock returns volatility on all other
Thursdays in our sample excluding MPC announcements for the same time frames. So if t
stands for the days of monetary policy decisions, and d=1,2…,D stands for the same weekdays
but when no MPC announcement has taken place, and R is the 5-minutes log returns then the
volatility ratio is given as follows:
)(1
)(
)(1
)(
1
]0,30[
]0,30[
1
]1,0[
]1,0[
]1,30[ D
d
d
m
t
m
D
d
d
h
t
ht
hm
RabsD
Rabs
RabsD
RabsvolR . (7)
We now regress these two variables on the same independent variables as in Eq. (2),
except that now we use the absolute value of the surprise. Results from the M estimation of
these regressions are reported in Table 4. Our results show that QE surprises increase equities
volatility on MPC meetings preceding by a week the inflation report release (reaction estimate
to the interactive term I3 x abs|St| is positive and statistically significant), unless these MPC
meetings follow news about unanimity in the previous MPC meeting when we report a negative
marginal reaction (reaction estimate to the interactive term IUNA x abs|St| is negative and
statistically significant). Considering that MPC meetings directly preceding the inflation report
release might be perceived as bearing news about the forthcoming inflation report, this
speculation appears to be increasing volatility. Moreover, we find that the QE news directly
following news about unanimity in the most recent MPC meeting decreases volatility in the
equity market, as possibly investors uniformly incorporate the news in their equity pricing
models.
4. Concluding Remarks
19
This paper considers the effects of the UK’s QE program on equity prices and their volatility.
We use an event-study framework and intra-day data to characterize the equity prices reactions
to BoE’s QE announcements. The key contributions of the paper include the relatively
unexplored to date effects of QE on stock price volatility and the association of the magnitude
of the pass-through of QE news into UK equities with the MPC framework. To capture the last,
we focus on two key paraphernalia of inflation targeting, namely the publication of inflation
reports and of the MPC members voting decision.
Our results are generally indicative of a statistically significant relationship between
QE surprises and equity returns on the days of MPC meeting announcements, which, however,
is of small magnitude. Although our evidence reiterates prior findings about a statistically
significant impact of QE announcements on intraday UK equity prices (Rogers, et al. 2014),
we also provide a comprehensive analysis of the time dimension of this impact, and of the role
of BoE’s communication policy. Moreover, we find a significant pre-announcement upward
drift in UK equity prices during the period considered, which partly accounts for the less
pronounced impact of QE announcements on equities.
Our evidence suggests that equity markets react differently to QE news in the hour
following the announcement and in the hours until the end of the trading day. In particular, in
the first hour following the MPC meeting announcements, equities react significantly and in a
manner intuitively expected only to those MPC meetings announcements following news about
a unanimous decision in the previous MPC meeting. QE news from these MPC meetings
announcements also appear to reduce stock price volatility. When the impact of QE news from
MPC meeting announcements preceding by a week the inflation report release is considered,
however, the results reveal a different pattern. This QE news appears not only to increase
volatility in equity markets during the hour following the announcement, but also the equities’
reaction is confusing. Smaller than expected asset purchases are now perceived as positive
20
news leading to slightly higher equity prices, as perhaps they are perceived to be indications of
the news included in the forthcoming inflation report.
In our study, while equities during the first hour following an announcement are
sensitive to news from MPC meetings attracting media attention (e.g., unanimous decisions
and imminent inflation report releases), when the wider window is considered a different
picture emerges. Equities returns and volatility appear to respond significantly, both in
magnitude and statistically, only to QE surprises emerging from the second MPC meetings
following inflation report releases. These MPC meetings occur almost two months after the
previous inflation report release and at least a month further from the new inflation report,
reinforcing the view that the inflation report is a dominant channel of BoE’s information
dissemination process.
In general, we find evidence of a significant impact of QE surprises on UK equities.
The communication framework of the BoE is an important factor determining the pass-through
of QE announcements to the stock market. The inflation report release emerges as a reference
point for the BoE communication and news about the MPC decisions unanimity appears to
increase the magnitude of the transmission. The results from the UK experience offer the
benefit of hindsight to think about the effectiveness of similar QE programs such as that of the
ECB, which is at its early stages of implementation. The increasing emphasis on the unanimity
of decision put by the ECB president's introductory statement to the press conference and the
corresponding media interest, signifies the importance of obtaining a better understanding of
the role of central banks’ communication.
21
REFERENCES
ANDERSSON, M., 2010. Using Intraday Data to Gauge Financial Market Responses to
Federal Reserve and ECB Monetary Policy Decisions. INTERNATIONAL JOURNAL OF
CENTRAL BANKING, 6(2), pp. 117-146.
BERNANKE, B.S. and KUTTNER, K.N., 2005. What Explains the Stock Market's Reaction
to Federal Reserve Policy? The Journal of Finance, 60(3), pp. 1221-1257.
BLINDER, A. S., WYPLOSZ, C., 2005. Central bank talk: Committee structure and
communication policy. Presented at the ASSA meetings, Philadelphia, January.
BREEDON, F., CHADHA, J.S. and WATERS, A., 2012. The financial market impact of UK
quantitative easing. Oxford Review of Economic Policy, 28(4), pp. 702-728.
CAHILL, M.E., D’AMICO, S., LI, C. and SEARS, J.S., 2013. Duration Risk versus Local
Supply Channel in Treasury Yields: Evidence from the Federal Reserve's Asset Purchase
Announcements. Finance and Economics Discussion Series 2013-35. Board of Governors of
the Federal Reserve System (U.S.).
CHORTAREAS, G. and NOIKOKYRIS, E., 2014. Monetary policy and stock returns under
the MPC and inflation targeting. International Review of Financial Analysis, 31(0), pp. 109-
116.
CHULIÁ, H., MARTENS, M. and DIJK, D.V., 2010. Asymmetric effects of federal funds
target rate changes on S&P100 stock returns, volatilities and correlations. Journal of Banking
& Finance, 34(4), pp. 834-839.
D’AMICO, S. and KING, T.B., 2013. Flow and stock effects of large-scale treasury purchases:
Evidence on the importance of local supply. Journal of Financial Economics, 108(2), pp. 425-
448.
EHRMANN, M. and FRATZSCHER, M., 2004. Taking Stock: Monetary Policy Transmission
to Equity Markets. Journal of Money, Credit and Banking, 36(4), pp. 719-737.
EHRMANN, M. and FRATZSCHER, M., 2007. Communication by central bank committee
members: different strategies, same effectiveness? Journal of Money, Credit and Banking,
39(2/3), 509-541.
EHRMANN, M. and SONDERMANN, D., 2012. The News Content of Macroeconomic
Announcements: What if Central Bank Communication Becomes Stale? International Journal
of Central Banking, 8(3), pp. 1-53.
GAGNON, J., RASKIN, M., REMACHE, J. and SACK, B., 2011. The Financial Market
Effects of the Federal Reserve’s Large-Scale Asset Purchases. INTERNATIONAL JOURNAL
OF CENTRAL BANKING, 7(1), pp. 3-43.
GERD, H. LUNDE, A. SHEPHARD, N. AND SHEPPARD, K. (2009) "Oxford-Man Institute's
realized library v0.2", Oxford-Man Institute, University of Oxford.
22
GLICK, R. and LEDUC, S., 2012. Central bank announcements of asset purchases and the
impact on global financial and commodity markets. Journal of International Money and
Finance, 31(8), pp. 2078-2101.
GOSPODINOV, N., GAVALA, A. and JIANG, D., 2006. Forecasting volatility. Journal of
Forecasting, 25(6), pp. 381-400.
GOSPODINOV, N. and JAMALI, I., 2012. The effects of Federal funds rate surprises on S&P
500 volatility and volatility risk premium. Journal of Empirical Finance, 19(4), pp. 497-510.
GÜRKAYNAK, R.S. and WRIGHT, J.H., 2013. Identification and Inference Using Event
Studies. The Manchester School, 81, pp. 48-65.
JOYCE, M., LASAOSA, A., STEVENS, I. and TONG, M., 2011. The Financial Market Impact
of Quantitative Easing in the United Kingdom. INTERNATIONAL JOURNAL OF CENTRAL
BANKING, 7(3), pp. 113-161.
JOYCE, M.A.S., MCLAREN, N. and YOUNG, C., 2012. Quantitative easing in the United
Kingdom: evidence from financial markets on QE1 and QE2. Oxford Review of Economic
Policy, 28(4), pp. 671-701.
JOYCE, M.A.S. and TONG, M., 2012. QE and the Gilt Market: a Disaggregated Analysis*.
The Economic Journal, 122(564), pp. F348-F384.
JUBINSKI, D. and TOMLJANOVICH, M., 2013. Do FOMC minutes matter to markets? An
intraday analysis of FOMC minutes releases on individual equity volatility and returns. Review
of Financial Economics, 22(3), pp. 86-97.
KRISHNAMURTHY, A. and VISSING-JORGENSEN, A., 2011. The Effects of Quantitative
Easing on Interest Rates: Channels and Implications for Policy. Brookings Papers on Economic
Activity, 43(2 (Fall)), pp. 215-287.
LUCCA, D.,O and MOENCH, E., 2015. The Pre-FOMC Announcement Drift. Journal of
Finance, 70(1), pp. 329-371.
MCLAREN, N., BANERJEE, R.N. and LATTO, D., 2014. Using Changes in Auction Maturity
Sectors to Help Identify the Impact of QE on Gilt Yields. The Economic Journal, 124(576),
pp. 453-479.
MEANING, J. and ZHU, F., 2011. The impact of recent central bank asset purchase
programmes. BIS Quarterly Review, December, pp. 73-83.
MELVIN, M., SABOROWSKI, C., SAGER, M. and TAYLOR, M.P., 2010. Bank of England
Interest Rate Announcements and the Foreign Exchange Market INTERNATIONAL
JOURNAL OF CENTRAL BANKING, 6(3), pp. 211-247.
NEELY, C.J., 2015. Unconventional monetary policy had large international effects. Journal
of Banking & Finance, 52, pp. 101-111.
23
ROGERS, J.H., SCOTTI, C. and WRIGHT, J.H., 2014. Evaluating asset-market effects of
unconventional monetary policy: a multi-country review. Economic Policy, 29(80), pp. 749-
799.
ROSA, C., 2012. How "Unconventional" Are Large-Scale Asset Purchases? The Impact of
Monetary Policy on Asset Prices. Federal Reserve Bank of New York Staff Reports 560, (May).
SWANSON, E., 2011. Let's Twist Again: A High-Frequency Event-study Analysis of
Operation Twist and Its Implications for QE2. Brookings Papers on Economic Activity, 42(1
(Spring)), pp. 151-207.
THORNTON, D.L., 2013. The Identification of the Response of Interest Rates to Monetary
Policy Actions using Market-Based Measures of Monetary Policy Shocks. Oxford Economic
Papers,66(1), pp. 67-87.
WRIGHT, J.H., 2012. What does Monetary Policy do to Long-term Interest Rates at the Zero
Lower Bound?*. The Economic Journal, 122(564), pp. F447-F466.
24
TABLES AND FIGURES
TABLE 1
QE SURPRISES AND UK EQUITY RETURNS
(1) (2) (3) (4)
c .006
(0.21)
0.04
(0.48)
.008
(0.29)
-.001
(-0.01)
St -.004
(-1.05)
0.03**
(2.43)
- -
I1 St - - 0.03
(1.53)
-0.01
(-0.15)
I2 St - - 0.01
(0.43)
0.18**
(2.18)
I3 St - - -0.06**
(-2.28)
-0.07
(-0.86)
IUNA St - - 0.06**
(2.10)
0.13
(1.36)
IAP St - - -0.01
(-0.57)
-0.15*
(-1.81)
R2(%) 2.17 6.37 11.39 15.24
Notes: In columns (1) and (2), we report results from the estimation of
Eq. (1). Two different event windows for the calculation of stock
returns are employed; Both start 10 minutes before the MPC
announcement and the narrow one ends 1 hour after the announcement
(r[-10,+1h]), while the wider one extends up to the closing of the trading
day (r[-10,close]). St denotes the unexpected element of the MPC’s QE
announcement, which is calculated as the difference between the
actual asset purchases of the Bank and the mean of economists’
estimates regarding the amount of Bank’s asset purchases taken by
Bloomberg’s survey. We examine 55 MPC announcements starting
from September 2009 when the Bloomberg survey data are available
until March 2014. In columns (3) and (4) we report the results from
Eq. (2) where I1 (I2 / I3) are 0-1 dummy variables taking the value of 1
on first (second / third) MPC meeting following the release of the
inflation report and zero otherwise. IUNA is a 0-1 dummy variable
taking the value of 1 on MPC meeting days directly following MPC
meeting minutes releases indicating unanimity in the decision of the
previous MPC meeting about asset purchases.
*/**/*** denote significance at 90%, 95%, and 99% confidence levels
respectively.
hr 1,10 closer ,10 hr 1,10 closer ,10
25
TABLE 2
PRE-MPC Announcement Returns (1) (2) (3) (4) (5) (6) (7)
(excl. top/bottom 1%)
(excl. top/bottom 1%)
c -0.03*
(-1.70) 0.01
(0.33) -0.03*
(-1.70) 0.02
(0.71) 0.10
(1.13)
0.14
(1.44)
0.14
(1.36) MPCpre
tI 0.17
(1.62) 0.24
(1.54) 0.07
(0.88) 0.17
(1.18) - - -
Δ(IP)t - - - - 0.23*
(1.88)
- -
Δ(INF)t - - - - 0.14
(1.18)
- -
(FTSE-IVI) t - - - - - 0.29***
(2.79)
-
S t - - - - - - 0.15***
(9.50)
Obs. 1,150 1,150 1,128 1,128 55 55 55
MPC Ann. 55 55 54 54 55 55 55
Notes: This table reports the results from Eq. (3) in the main body of the text. MPCpreI
is a dummy variable taking the value of 1
on the 55 pre-announcement windows which are directly followed by MPC announcements and zero otherwise. Δ(IP)t denotes the
annual growth in the industrial production index and Δ(INF)t is the annual growth in Consumer Price Index. (FTSE IVI)t stands for
the level of the FTSE 100 implied volatility index on the closing two days before the MPC announcement. St is the unexpected
element of the MPC’s quantitative easing announcement. Huber-White standard errors for the estimates are reported in the
parentheses.
*/**/*** denote significance at 90%, 95%, and 99% confidence levels respectively.
]55:118[ amamr ]55:1112[ ampmr
]55:118[ amamr ]55:1112[ ampmr
]55:118[ amamr ]55:118[ amamr ]55:118[ amamr
26
TABLE 3
QE SURPRISES AND DAILY CHANGES IN EQUITY VOLATILITY
(1) (2) (3) (4) (5)
ΔIV ΔRV βIV=βRV
[Sign.]
ΔRVG ΔRVC
c -0.75***
(-2.99)
1.08***
(3.22)
[0.00] -0.07
(-1.01)
1.08***
(2.54)
I1 St 0.12
(0.63)
0.10
(0.39)
[0.93] .004
(0.07)
0.09
(0.28)
I2 St -0.15
(-0.66)
0.71**
(2.31)
[0.03] -0.06
(-0.84)
0.77**
(2.00)
I3 St 0.02
(0.08)
0.48
(1.57)
[0.24] 0.02
(0.23)
0.51
(1.30)
IUNA St -0.18
(-0.66)
-0.28
(-0.77)
[0.83] -0.02
(-0.31)
-0.33
(-0.72)
IAP St 0.10
(0.42)
-0.66**
(-2.17)
[0.05] -.002
(-0.03)
-0.76**
(-1.96)
R2(%) 8.07 6.56 - 6.52 9.16
Notes: This table displays the results from the M-estimation of Eq. (4). ΔIV is the daily
change in implied volatility taken by FTSE-100 implied volatility index. ΔRV denotes
the daily change in realized volatility taken from Oxford-Man Institute’s “realized
library” (Gerd et al., 2009). Column (3) reports the p-value of an equality test of the
estimates from regressions in columns (1) and (2). ΔRVG and ΔRVG stand for the daily
change of stock market’s realized volatility obtained from Eq. (5) and Eq. (6)
respectively.
*/**/*** denote significance at 90%, 95%, and 99% confidence levels respectively.
27
TABLE 4
QE SURPRISES AND INTRA-DAY VOLATILITY
(1) (2)
ΔRVG ΔVolR
c 3.05***
(15.16)
-0.13
(-1.06)
I1 |abs|St 0.09
(0.58)
0.07
(0.77)
I2 |abs|St 0.04
(0.23)
0.15
(1.32)
I3 |abs|St 0.38**
(2.08)
0.33***
(2.96)
IUNA |abs|St -0.46**
(-2.16)
-0.24*
(-1.85)
IAP |abs|St 0.12
(0.67)
-0.08
(-0.71)
R2(%) 13.98 18.36
Notes: This Table reports the results from the M-estimation of
Eq. (4). ΔRVG is the realized volatility of equities from 10-
minutes before the announcement until 1 hour after the
announcement calculated by Eq. (6). ΔVolR is the volatility ratio,
calculated by Eq. (7), showing the difference between the
volatility ratio for FTSE-100 index returns for the hour following
the MPC announcement and the volatility ratio for the 30 minutes
before it. |abs|St is the absolute value of the unexpected element
of an MPC announcement.
*/**/*** denote significance at 90%, 95%, and 99% confidence
levels respectively.
28
FIGURE 1
CUMULATIVE STOCK RETURNS ON FTSE 100 STOCK PRICE INDEX.
Notes: The solid line depicts the average cumulative 5-minute returns on the 55 Thursdays
of MPC announcement days from September 2009 to March 2014. The dashed line depicts
the average cumulative 5-minute returns on all Thursdays in our sample excluding those
which have an MPC announcement. 95% confidence intervals from Newey-West standard
errors for each point wise cumulative mean return includes the zero point suggesting that
statistically it is not statistically different from zero. The vertical dashed line points the
time of the MPC announcement.
-0.1
-0.05
0
0.05
0.1
0.15
0.28
:00
8:2
0
8:4
0
9:0
0
9:2
0
9:4
0
10:0
0
10:2
0
10:4
0
11:0
0
11:2
0
11:4
0
12:0
0
12:2
0
12:4
0
13:0
0
13:2
0
13:4
0
14:0
0
14:2
0
14:4
0
15:0
0
15:2
0
15:4
0
16:0
0
16:2
0
MPC Announcement
29
FIGURE 2
THE UNEXPECTED COMPONENT OF BANK’S ASSET PURCHASES ANNOUNCEMENT.
A. Actual vs. forecasted size of APP B. Monetary Surprises
Notes: The dashed line in Panel A of this figure reports the actual size of the Bank’s APF program as announced
on each of the 55 MPC meetings, while the solid line depicts the average of the estimates provided by economists
taking part in Bloomberg’s survey preceding the MPC meeting. Monetary surprises in Panel B show the difference
between the actual minus the expected size of the Bank’s APF program.
150
200
250
300
350
400
Sep
-09
Mar
-10
Sep
-10
Mar
-11
Sep
-11
Mar
-12
Sep
-12
Mar
-13
Sep
-13
Mar
-14
actualexpected
£56.25b
45
60
Sep
-09
Mar
-10
Sep
-10
Mar
-11
Sep
-11
Mar
-12
Sep
-12
Mar
-13
Sep
-13
Mar
-14