1 Introduction
One of the major purposes of bank regulation is to ensure institutions maintain safe and sound business practices, by conducting supervision and, in particular, bank safety and soundness examinations (Curry et al. 1999). Enforcement actions (hereinafter referred to as EAs) are an essential part of the supervisory mechanism that ensure actual operations are consistent with sound practises and represent the most vital component of effective banking supervision (Delis et al. 2013). When unsafe or illegal activities are identified, regulators have the power to enforce sanctions by imposing appropriate corrective actions, compelling safe practises as well as inducing an alteration in banks’ behaviour, thereby averting future potential losses and ensuring stability and soundness. In the execution of their supervisory activities, banking regulators can take a variety of formal or informal EAs1 against financial institutions and their affiliated parties in case of violations of laws, rules or regulations, unsafe or unsound practices, breaches of fiduciary duty and violations of final orders.2
EAs could be idiosyncratic in nature as well as reflect market conditions and/or supervisory focus at a specific point in time (Srinivas et al. 2015). Moreover, as formal EAs are publicly available, sanctioned institutions experience both direct (i.e. financial penalty, actions to correct the problem identified) and indirect costs (i.e. reputational loss, panic among investors).
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Banking supervisory actions aim to prevent the occurrence of systemic risk in the banking sector as well as to increase transparency and contribute to the protection of small depositors (Davis and Obasi 2009). However, following the financial crisis, there is a growing need for a fresh reconsideration in the approach of banking supervision and the effectiveness of the corrective actions, in the interest of banks themselves and their stakeholders.
Previous studies have investigated the impact of EAs on bank capital, risk and performance (i.e. Curry et al. 1999; Delis and Staikouras 2011; Chortareas et al. 2012; Delis et al. 2013; Filotto et al. 2014) and found conflicting evidence. Recent studies also focus on the effect of EAs on the real economy (Danisewicz et al. 2014) and corporate culture (Cerqueti et al. 2016). However, there is limited literature that investigates how financial markets react to supervisory actions (i.e. Brous and Leggett 1996; Jordan et al. 1999; Zeidan 2013; Ren 2015) and depositors’ disciplining mechanism (i.e. Gilbert and Vaughan 2001; Semenova 2007). To the best of our knowledge, there is no thorough investigation of how key bank stakeholders, i.e. shareholders and depositors, react to US banks EAs.
Investigating whether and how equity market and depositors respond to the announcement of EAs in the banking sector is a relevant issue due to the crucial role of banks in the financial system. Indeed, the banking industry is heavily regulated, in the interest of depositors as well as to safeguard integrity and the reputation of the financial system (Zeidan 2013). By compelling banks to implement corrective actions, adopt safe practices, incur civil money penalties, among others, EAs have the potential to affect banks’ operations, profitability, and valuation, and can be seen as an indicator of unsafe or unsound operations. Therefore, apart from being a supervisory discipline mechanism issued to sanction bank misconduct, EAs represent a wider action involving customer protection, market integrity, safety, soundness, and corporate governance. On the one hand, EAs may lead to an overreaction by shareholders and investors, affecting share price and cost of capital (Zeidan 2013). Indeed, when deciding to purchase bank equity, investors assess that the bank is safe and sound, and that the investment yields the expected return (Bruno et al. 2016); EAs may therefore lead investors to revise their expected returns and their investment decisions on bank equity. On the other hand, depositors may be unwilling to bring money to a bank with uncertain liquidity and solvency (Semenova 2007); depositors may panic and can either withdraw funds or demand higher returns (Gilbert and Vaughan 2001). As a result, investors and depositors may be reluctant to provide funds to banks following EAs, and in the worst case scenario, this loss of investor and depositor confidence can lead to systemic repercussions that would require further intervention (Jordan et al. 1999; Gilbert and Vaughan 2001; Bruno et al. 2016).
Within this context, we investigate market movement and depositors’ reactions following EA announcements in the US banking sector over the period 2004-2015. First, we build a unique dataset of EA announcements issued by US supervisory authorities. This sample of sanctioned banks is matched to a sample of comparable non-sanctioned banks by applying a propensity score matching (PSM) methodology. Second, we investigate the market reaction following the announcement of EAs, using event study methodology and testing for causality to answer the following question: How does the equity market react to the different types of EA announcements in the US banking system? Third, we investigate depositors’ reaction to EAs to address the second research question: How do depositors react to the different types of EA announcements in the US banking system?
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The main results show that equity market reacts negatively following cease and desist (C&D) announcements, while weak or no reaction is found for other EA types, documenting the ability of equity market to discriminate EAs based on their severity. Moreover, a negative market reaction following C&D announcements suggests that more severe EAs are not fully anticipated by the market. These findings are robust when comparing sanctioned banks with non-sanctioned ones. Depositors exhibit different behaviour depending on the type of sanction and the type of deposit considered. Demand depositors penalize sanctioned banks following C&D announcements. However, a positive effect on depositors can be noted following FA announcements, suggesting depositors perceive FA to be a corrective mechanism. Robustness checks on both sanctioned and non-sanctioned banks further validate these results.
This research complements the existing literature on bank EAs, by providing new empirical evidence on the impact of EAs on key bank stakeholders, i.e. shareholders and depositors. We contribute to previous literature (i.e. Brous and Leggett 1996; Gilbert and Vaughan 2001; Zeidan 2013) by providing empirical evidence across a range of EA types (cease and desist, civil money penalty, formal agreements) and deposit types (saving, demand, time, core). To this aim, we use a more recent, manually collected and wider dataset on different types of sanctions enforced by Board of Governors of the Federal Reserve System (FED), Office of the Comptroller of the Currency (OCC), and Federal Deposit Insurance Corporation (FDIC) on US banks, thus enhancing the scope of investigation. We complement previous studies (i.e. Gilbert and Vaughan 2001; Zeidan 2013) by testing for causality of EA announcements on market and depositors’ reaction, thus enhancing the reliability of the findings. Differently from previous studies, the analysis is carried out for both the sanctioned banks as well as comparable non-sanctioned banks identified using PSM methodology, thus further validating the cause-effect relationship. By providing an in-depth empirical analysis on the effect of supervisory actions on key bank stakeholders, this study provides a better understanding of how EAs are perceived by shareholders and depositors; this can guide banks’ behaviour, drive future policy interventions and contribute to enhance supervisory effectiveness.
The remainder of the paper is organized as follows. Section 2 reviews the existing literature and identifies the research hypotheses. Section 3 defines the sample selection process and the methodology. Section 4 discusses the empirical results and Section 5 concludes the paper.
2 Literature
The analysis on the effects of regulatory EAs on banking institutions is a wide research field. Most of the existing literature investigates the impact of EAs on banks’ behaviour, specifically looking at capital, risk and performance (Section 2.1). Further literature focuses on previous studies related to market reaction (Section 2.2) and depositors’ reaction (Section 2.3).
2.1 The Effect of Enforcement Actions on Banks
A substantial stream of literature investigates the effect of EAs on bank capital, risk and performance, and finds contrasting evidence. Peek and Rosengren (1995) examine supervisors’ intervention when a bank’s financial situation deteriorates and find formal regulatory actions that require higher bank capital ratios lead to reductions in bank lending. Further, few banks are able to raise new equity at a reasonable cost, while most banks need to decrease their assets (Peek and Rosengren 1996). Within this field, focusing on US financially distressed banks during 1980-1996, Curry et al. (1999) find that banks that received formal actions had more pronounced changes in their performance measures than the banks that experienced a downgrade in their CAMELS3 rating. Moreover, EAs are found to be more effective in correcting weaknesses that bank management can control (i.e. cash dividends, loan-loss provisions and loan charge-offs) than areas where management has limited control (i.e. external capital injections, asset growth).
From the risk perspective, Delis and Staikouras (2011) examine how banking supervision across 17 countries over the period 1998-2008 is able to control bank risk and find a non-linear relationship between on-site audits and bank risk, while a linear negative relationship exists between sanctions and risk. In a further paper, they extend this study to the impact of EAs on US banks’ risk-based capital, risk and performance over the period 2000-2010 (Delis et al. 2013); following an EA, risk-weighted capital falls, the risk-weighted asset ratio declines to levels approximately equal to the industry average, while profitability increases. Chortareas et al. (2012) analyse the relationship between bank supervision, regulation and efficiency for a sample of commercial banks operating in 22 EU countries from 2000 to 2008. Their results show that strong capital restrictions and official supervisory powers can improve the efficient operation of banks, and these beneficial effects are more pronounced in countries with better quality institutions.
Focusing on the Italian banking system, Brogi (2011) shows that administrative sanctions issued by the Bank of Italy from 1998-2009 are not effective in disciplining board members or banks, recidivism is extremely widespread and sanctions do not prevent re-election of the same bank board members. Within the same context, Filotto et al. (2014) find that administrative sanctions issued by the Bank of Italy over 2005-2012 are not effective in improving bank risk profile and performance; in fact, banks receiving sanctions are riskier, less profitable, and less capitalized than non-sanctioned ones.
More recent research focuses on the effect of EAs on other factors including the real economy and corporate culture (Danisewicz et al. 2014; Cerqueti et al. 2016). Danisewicz et al. (2014) show that regulatory EAs on banks trigger significant adverse effects on the macro economy; in particular, severe actions like cease and desist orders imposed on single-market banks reduce personal income growth in US rural counties. Cerqueti et al. (2016) examine if supervisory actions influence bank culture using a sample of EAs on US banks for 2006-2013. Their results show that low regulatory capital ratios, low performance and high credit-risk indicators tend to attract EAs. Banks with high probability of being sanctioned tend to become more conservative and prudent along internal cultural dimensions and changes in culture appear unrelated to changes in bank activity and capital adequacy ratios.
However, none of the above studies investigates the impact of EAs on banks’ stakeholders. To the best of our knowledge, there is limited research on the effects of EAs in particular on the equity market and depositors. Moreover, supervisors can enforce different types of sanctions depending on the magnitude and seriousness of violations from the prescribed banking practices; however, previous literature does not always make a clear distinction based on the type of EA. This study contributes to the existing literature by investigating how equity market and depositors react to the announcement of different types of EAs in the US banking sector.
2.2 Enforcement Actions and Market Reaction
The relationship between EAs and market reaction has been investigated by previous studies (Brous and Leggett 1996; Jordan et al. 1999; Zeidan 2013; Ren 2015). Seminal empirical evidence comes from Brous and Leggett (1996) that examine stock price reaction to EAs, including cease and desist orders and written agreements, for a sample of US commercial banks from 1989-1991. They find significant negative abnormal returns, suggesting EAs are not fully anticipated by the market and, on average, are perceived as unfavourable for bank shareholders. Similarly, Jordan et al. (1999) find the announcement of formal EAs to be informative for stock market participants, resulting in a large negative abnormal stock return for sanctioned banks. Moreover, improving disclosure requirements for troubled US banks during the banking crisis allowed market discipline to work more effectively, thus supporting the public policy proposal of enhanced bank disclosure, even in periods of banking crisis. However, changes in the regulatory environment over the last decade justify a re-investigation of the issue focusing on a more recent timeline. Moreover, it is worth differentiating the analysis by event type and testing the cause-effect relationship using a more robust methodology. Market reaction to supervisory sanctions is also reported in Ren (2015) that finds a negative market reaction to EAs for related party transactions from 2000-2013; however, this analysis refers to non-financial companies only and is limited to the effect on the Chinese stock market.
Recent empirical evidence on the relationship between EAs and market reaction in the US banking system comes from Zeidan (2013). Focusing on a sample of 128 publicly traded US banks that were subject to EAs over the period 1990-2009, Zeidan (2013) documents a significant negative market reaction to EAs, while the seriousness of the violation and the existence of multiple violations are found to be insignificant. Violating laws and regulations negatively affects the valuation of sanctioned banks as evident from the negative reaction documented in event studies. However, the analysis is limited to event study methodology, for a restricted event window, with no causal inference. Moreover, the analysis does not differentiate across EAs types, each of them representing different levels of severity, and therefore may lead to different market reactions. Therefore, it is important to further investigate the phenomenon by widening the scope of empirical investigation.
We contribute to previous literature by providing new empirical evidence on the impact of US banks EAs on the equity market. We complement previous literature by using a wider sample and a more robust methodology; in addition to event study methodology introduced for a range of event windows, we test for cause-effect relationships between EAs and the market reaction for a recent time period. Further, we analyse a range of EA types and validate our analysis by testing across both sanctioned and comparable non-sanctioned banks. In line with previous literature, we expect equity market to react negatively to the announcement of EAs in the US banking system (H1).
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H 1 : Equity market reacts negatively to the announcement of EAs on US banks.
2.3 Enforcement Actions and Depositors’ Reaction
Bank deposits are a crucial component of bank balance sheets and a field of existing literature investigates the factors affecting bank deposit growth. Within this field, the growth of deposits is found to be driven by both supply-side (income, inflation, interest rates, risk-reward profile of investment alternatives, demography, stability and trust in the banking sector) and demand-side components (regulation, competition, cost and availability of external funds) (Ahlswede and Schildbach 2012). Moreover, some literature documents bank disciplining power exercised by depositors. An empirical analysis on Russian banks over 2004-2006 (Semenova 2007) shows that depositors of private domestic banks discipline their banks by quantity (choosing bigger banks in terms of assets), by price and by switching from on-call to long-term deposits. Finger and Hesse (2009) examine the demand for commercial bank deposits in Lebanon and identifies macro- (economic activity, price and interest differential) and micro-level factors (bank risk, liquidity, loan exposure, interest margin) affecting deposit demand. Berger and Turk-Arris (2015) find significant depositor discipline prior to the crisis for US and EU with a decline following the crisis except for small US banks; their results vary based on bank size and bank listing status. Davenport and McDill (2006) examine disciplinary behaviour of both insured and uninsured depositors for a failed bank between March 2001 and January 2002. Their findings confirm the existence of a depositor disciplining mechanism, thus extending previous literature on potential sources of depositor discipline to include fully insured depositors. However, none of the above studies analyse depositors’ behaviour following formal sanctions enforced on their banks.
Within this field of research, it is interesting to investigate whether and how depositors react to the announcement of EAs. The earliest empirical evidence on this topic comes from Gilbert and Vaughan (2001) that measure depositors’ reaction to 87 Federal Reserve EA announcements, by comparing deposit growth rates and yield spreads before and after the announcements for sanctioned banks and a control group of peer banks. Their results show that depositors do not care a great deal about EAs, and their study fails to document unusual deposit withdrawals or spread increases. This implies public announcements of EAs do not spark bank runs or enhance depositor discipline. However, their methodology is limited to mean deposit growth rate comparison and does not provide causality inference; therefore, it is worth investigating the phenomenon by widening the empirical investigation.
We extend previous literature by providing new empirical evidence on depositors’ reaction to EA announcements. Our work differs from Gilbert and Vaughan (2001) in the sense that we use a wider and recent sample, and a more robust methodology to test depositors’ reaction following EAs. Moreover, we complement previous literature by analysing a range of EA types and a set of depositor types. We extend previous literature by testing for causal between EA announcements and depositors’ reaction, and validate our results across both sanctioned and comparable non-sanctioned banks using PSM methodology.
All deposits are characterized by some probability that the bank will not be able to repay due to default, however depositors' ability to change characteristics of their deposits in response to excessive risk-taking is questionable. Also, depositors would be unwilling to bring money to a bank which has uncertainty over its liquidity and solvency (Semenova 2007). At the same time, supervisors fear that, when negative information is released, depositors will panic and withdraw funds from the bank rather than evaluate the information carefully. In theory, depositors should respond by withdrawing funds or demanding higher returns on those funds (Gilbert and Vaughan 2001). In line with these arguments, we expect depositors to react negatively following EAs announcements affecting their banks (H2).
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H 2 : Depositors react negatively to the announcement of EAs on US banks.
3 Methodology
The aim of this section is to describe the methodology used for empirical analysis. Section 3.1 describes the sample selection process of EA announcements. Section 3.2 details the process for building the control group of non-sanctioned banks. Section 3.3 defines the event study methodology. Sections 3.4 and 3.5 present the methodology used to test market movement and depositors’ reaction respectively.
3.1 Sample Description: EA Announcements
Data on formal EAs against banking institutions are manually collected from the websites of US supervisory authorities, namely the FED4, OCC5 and FDIC.6 This study focuses on, i) formal EAs that, differently from the informal actions, are publicly disclosed and ii) actions enforced on institutions operating in the US banking sector, without considering their affiliated parties. The timeline of analysis is January 2004 to August 2015 and includes three main types of sanctions: cease and desist orders (C&D)7, orders assessing civil money penalties (CMP)8 and formal agreements (FA).9
Table 1 summarises the sample selection process (Panel A) and the distribution of EAs by year (Panel B). In Panel A, the initial sample represents the EA events downloaded from the FED, OCC and FDIC, containing 956, 925 and 2096 EA announcements respectively. To evaluate the market reaction following the announcement of EAs, we exclude events for which neither the bank nor the parent is listed. Further, EAs are filtered to avoid duplication across the datasets. The above steps reduce the sample to 1526 EA announcements imposed on 423 unique banks over the period 2004-2015. The final sample of all banks collectively in our sample represents 61.39% of the US depository institutions in terms of total assets and 61.32% in terms of total deposits, as of 2015.10
Table 1
Sample description of EA announcements
Panel A- Sample Selection process | ||||
Database | FED | OCC | FDIC | Total |
EAs downloaded | 956 | 925 | 2096 | 3977 |
Neither Bank or Parent Listed | (585) | (453) | (1248) | (2286) |
Initial Sample | 371 | 472 | 848 | 1691 |
Removing duplicates | (165) | |||
Final Sample | 1526 | |||
Panel B – List of EAs by year | ||||
Year | C&D | CMP | FA | Total |
2004 | 23 | 29 | 13 | 65 |
2005 | 23 | 41 | 15 | 79 |
2006 | 18 | 39 | 13 | 70 |
2007 | 34 | 43 | 8 | 85 |
2008 | 59 | 43 | 34 | 136 |
2009 | 163 | 59 | 86 | 308 |
2010 | 62 | 71 | 120 | 253 |
2011 | 96 | 86 | 51 | 233 |
2012 | 31 | 49 | 51 | 131 |
2013 | 22 | 43 | 14 | 79 |
2014 | 16 | 28 | 7 | 51 |
2015 | 11 | 19 | 6 | 36 |
Total | 558 | 550 | 418 | 1526 |
% | 36.57 | 36.04 | 27.39 | 100 |
Panel B shows the distribution of EAs over 2004-2015, highlighting some notable differences in the number of EAs across the years, with a peak in the announcements following the financial crisis. For the period 2004-2008, an average of 87 formal EAs against US banks were issued each year; as expected, EAs significantly increased in 2009 and 2010, reaching the highest number of 308 EAs within the period analysed. This peak in EA announcements can be attributed to the financial crisis that negatively affected US bank’s capital, liquidity and performance (Srinivas et al. 2015). Specifically for C&D, across the period 2008 to 2011, C&D sanctions collectively account for 68.10% of the total C&D EAs across the period of analysis. Since 2012, the number of EAs has started declining; this may be due to improved financial soundness and compliance, a more positive market environment, and the failure of many weak institutions (Vartanian and Schleusener 2012; Srinivas et al. 2015). Overall, majority of EA announcements in the final dataset is composed of C&D (36.57%) followed by CMP (36.04%) and FA orders (27.39%).
For the most recent year observed, i.e. 2015, the sample includes 36 EAs issued on 18 unique banks, representing 4.63% of the total listed US banks.11 Overall, similarly low percentages are found across years (i.e. 6.74% in 2014, 10.13% in 2013), while showing a peak around the financial crisis period (38.25% in 2010, 37.64% in 2009).12
3.2 Estimation of Control Group
We follow Rosenbaum and Rubin (1983) and use propensity-score matching (PSM) methodology to build a control group and enable comparative evaluations between sanctioned and non-sanctioned banks. The PSM process reduces potential sample selection bias and restricts inference to the sample of sanctioned banks (treatment group, denoted Ti=1 for bank i) and non-sanctioned banks (control group, denoted Ti=0). The treatment group is matched with the control group on the basis of propensity score which is a function of banks observable characteristics (Xi).
$$ P\left({X}_i\right)= Prob\left({T}_i=1|{X}_i\right), with\ \left(0<P\left({X}_i\right)<1\right) $$
(1)
The matching process entails the following steps. First, we identify all active firms with SIC code starting with ‘60 - Depository Institution’ within the US from the Bloomberg database. This group represents the control sample base (N=876 banks). Second, for each year starting from 2004, we remove banks that have been sanctioned the previous year from control sample base. For all the sanctioned (treated) banks and the remaining non-sanctioned ones (control sample base), we estimate the propensity scores through a probit model based on a list of bank characteristics (size, efficiency and profitability) a year before the EA announcement. Third, using the nearest neighbour matching technique (Guo and Jiang 2013; Gangl et al. 2014), we identify a control bank that has the closest propensity score to that of the treatment bank in that year, without replacement. This process is repeated every year until 2015. This estimation process identifies a one to one match for 1056 EA announcements from the initial sample of 1526.13
3.3 Event Study Methodology
To test the first research hypothesis (H1), an event study methodology is used to assess the effect of EA announcements on bank share price. For each sanctioned bank, the market reaction is measured by the cumulative average abnormal return (CAAR) around the announcement date using a standard market model (MacKinlay 1997; Ricci 2015).Where Rit is the equity return for a bank (i) for a given day (t), Rmt is the return on the market for a given day (t), eit is the white noise random component which is not correlated with Rmt and is the statistical error term having an expected value E(eit) = 0, with a constant variance Var (eit) = σ2ei and E(eit, ei,t-j) = 0, for every i≠j, αi and bi are the model coefficients.
$$ {R}_{it}={a}_i+{b}_i{R}_{mt}+{e}_{it} $$
(2)
The ai and bi are estimated in an OLS regression setting using the daily log of share price returns obtained from Bloomberg. S&P 500 returns are used as the market index and the econometric estimation is carried out over a 232 day estimation window, ending 20 days before the announcement date, i.e. period between 252 and 21 trading days prior to the announcement day. The above specification provides estimation for the parameters of normal period model which is not influenced by the event-related returns.
The estimated coefficients are replaced in Eqn. (2), to calculate the expected return \( {\widehat{R}}_{it} \) for each firm (i). Abnormal return (ARi) for each firm (i) is derived using Eqn. (3),where \( {\widehat{R}}_{it}={a}_i+{b}_i{R}_{mt} \)
$$ {AR}_{it}={R}_{it}-{\widehat{R}}_{it} $$
(3)
The cumulative abnormal return (CAR) is introduced to accommodate multiple sampling intervals within the event window and CARi(t1t2) is the CAR for security (i) from t1 to t2 estimated as,
$$ {CAR}_i\left({t}_1,{t}_2\right)=\sum \limits_{t=t1}^{t2}{AR}_{it} $$
(4)
To aggregate ARs across securities and through time, we assume no significant correlation across ARs of the different securities.14 The average abnormal return (AAR) for a given t across securities is estimated as,where N is the number of banks that have actual equity return available for a given day t. To investigate the ongoing impact of an event on equity returns, AAR is aggregated through time,Where CAAR{t1, t2} is the cumulative average abnormal return for the period {t1, t2}. We focus on the following short event windows: 7 days [-1;+5], 5 days [-1;+3], 3 days [-1;+1], 2 days [0;+1] and 1 day [0] for event analysis.
$$ {AAR}_t=\frac{1}{N}\sum \limits_{i=1}^NA{R}_{it} $$
(5)
$$ {CAAR}_{\left\{t1,t2\right\}}=\sum \limits_{t=t1}^{t2}{AAR}_t $$
(6)
A series of parametric tests (standardised t - ZO, ZP (Patell 1976) and ZB (Boehmer et al. 1991)) and non-parametric tests (RT and RZ as estimates of rank test (Kolari and Pynnonen 2011) and SC (Cowan 1992) and ST (Corrado and Zivney 1992) as estimates of sign test) are applied to evaluate the statistical significance of CAAR.
3.4 Market Reaction to EA Announcements
To infer causality in the first research hypothesis (H1), we use OLS regression to examine the effect of sanction announcements on the equity market controlling for bank-specific, market and time period variables,
$$ {CAR}_{i,j}^{t_1,{t}_2}=\alpha +{\sum}_1^j{\beta}_j{EVENT}_{i,j}+{\sum}_1^k{\gamma}_k{BANK}_{i,k}+{\sum}_1^h{\delta}_h{MARKET}_h+{\sum}_1^n{\mu}_n{TIME}_n+{\varepsilon}_{i,j}^{t_1,{t}_2} $$
(7)
where the dependent variable is the cumulative abnormal return (CAR) for the i-th bank and the j-th announcement over the event window (t1, t2). Four variations of the event window, i.e. 1 day [0], 2 days [0;+1], 3 days [-1;+1] and 5 days [-1;+3], are tested in the regression model. EVENT is a vector of j categorical variables identifying the type of EA announcement (C&D_D, CMP_D and FA_D). BANK is a vector of k bank-specific variables (TOTAL ASSET, Z SCORE, EFFICIENCY, TIER1). MARKET is a vector of h market variables (S&P INDEX, PMI). TIME identifies dummy variables for the periods related to the financial crisis (SUBPRIME_D, GLOBAL_D). Bank specific and market variables are collected from Bloomberg on a quarterly frequency.
For a robustness check, the analysis is repeated by comparing the sample of sanctioned (Tg) and non-sanctioned banks (Cg),where TYPE_D is a dummy variable equal to 1 for Tg and 0 for Cg; the other variables are similar to as in Eqn. (7).
$$ {CAR}_{i,j}^{t_1,{t}_2}=\alpha +\beta TYPE\_{D}_i+{\sum}_1^k{\gamma}_k{BANK}_{i,k}+{\sum}_1^h{\delta}_h{MARKET}_h+{\sum}_1^n{\mu}_n{TIME}_n+{\varepsilon}_{i,j}^{t_1,{t}_2} $$
(8)
One quarter lag of independent variables is used to control for endogeneity in the above regression models. A detailed description of the variables is reported in Table 2.
Table 2
Descriptive Statistics
Panel A- Sanctioned banks
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Variables | Description | N | Mean | Med. | Min | Max | Stdev | Skew. | Kurt. |
CAR[0] | CAR on the day of the announcement reported in basis points | 1387 | 1.53 | 0.00 | -484.87 | 485.56 | 209.71 | 0.00 | 3.94 |
CAR[0,+1] | CAR for 2-day event window reported in basis points | 1387 | -16.28 | 0.00 | -729.35 | 641.98 | 308.54 | -0.23 | 3.64 |
CAR[-1,+1] | CAR for 3-day event window reported in basis points | 1387 | -23.55 | 0.00 | -928.22 | 772.94 | 385.19 | -0.34 | 3.58 |
CAR[-1,+3] | CAR for 5-day event window reported in basis points | 1387 | -29.43 | -3.13 | -1161.93 | 1037.88 | 498.44 | -0.18 | 3.47 |
CAR[-1,+5] | CAR for 7-day event window reported in basis points | 1387 | -35.70 | 0.00 | -1442.62 | 1184.58 | 590.61 | -0.33 | 3.55 |
TOTAL_DEP | growth in total deposits, estimated as In(Total depositQ/Total DepositQ-4) ∗ 100 | 43662 | 8.18 | 5.73 | -8.38 | 35.78 | 11.07 | 0.93 | 3.36 |
SAVING_DEP | growth in saving deposit, estimated as In(Saving DepositQ/Saving DepositQ−4) ∗ 100 | 41740 | 9.97 | 7.42 | -14.38 | 47.84 | 14.71 | 0.85 | 3.54 |
DEMAND_DEP | growth in demand deposit, estimated as In(Saving DepositQ/Saving DepositQ−4) ∗ 100 | 42727 | 11.65 | 9.64 | -10.75 | 47.28 | 14.01 | 0.81 | 3.36 |
TIME_DEP | growth in time deposit, estimated as In(Time DepositQ/Time DepositQ−4) ∗ 100 | 41930 | 8.60 | 5.07 | -9.91 | 44.93 | 13.30 | 1.24 | 4.16 |
CORE_DEP | growth in core deposit, estimated as In(Core DepositQ/Core DepositQ−4) ∗ 100 | 42445 | 1.93 | 0.00 | -34.25 | 45.37 | 20.06 | 0.32 | 2.75 |
TOTAL ASSET | logarithm of total assets | 44753 | 8.51 | 8.12 | 0.53 | 14.76 | 2.28 | 1.00 | 3.72 |
Z SCORE | bank risk estimated as (ROA + Equilty/Assets)/ÓROA | 40178 | 20.04 | 12.25 | -1.87 | 75.14 | 21.64 | 1.27 | 3.66 |
EFFICIENCY | cost to income ratio | 44625 | 66.53 | 64.48 | 43.02 | 104.59 | 14.94 | 0.88 | 3.56 |
TIER1 | Tier 1 capital ratio | 44120 | 12.51 | 12.16 | 7.54 | 18.98 | 2.97 | 0.46 | 2.58 |
NPLOANS | ratio of non-performing loans to total loans | 41718 | 1.73 | 1.07 | 0.15 | 6.96 | 1.77 | 1.61 | 4.87 |
LOANS_GR | growth in total loans, estimated as 𝑙𝑛In(Total LoansQ/Total LoansQ−4) ∗ 100 | 43485 | 8.10 | 6.09 | -11.25 | 36.06 | 11.77 | 0.68 | 3.05 |
S&P INDEX | annualised return on past 250 days S&P index | 57408 | 1.87 | 2.30 | -2.70 | 4.60 | 1.97 | -0.77 | 2.91 |
PMI | proxy for economic health of the US manufacturing sector | 57408 | 0.09 | 0.06 | -0.42 | 0.54 | 0.27 | -0.19 | 2.40 |
GDP | gross domestic product of the bank country indexed using Q1 2003 as base | 57408 | 0.18 | 0.20 | -0.30 | 0.80 | 0.26 | 0.38 | 3.16 |
Panel B: Matched non-sanctioned banks
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Variable | N | Mean | Median | Minimum | Maximum | Stdev | Skewness | Kurtosis | |
TOTAL_DEP | 1041 | 6.91 | 4.91 | -8.23 | 32.24 | 9.79 | 0.98 | 3.62 | |
SAVING_DEP | 983 | 8.52 | 6.26 | -18.17 | 44.86 | 14.98 | 0.64 | 3.18 | |
DEMAND_DEP | 988 | 10.65 | 8.39 | -11.34 | 44.78 | 14.01 | 0.77 | 3.17 | |
TIME_DEP | 1024 | 7.75 | 4.00 | -11.94 | 44.76 | 13.22 | 1.31 | 4.45 | |
CORE_DEP | 994 | 1.06 | 0.00 | -33.13 | 44.78 | 19.39 | 0.43 | 3.00 | |
TOTAL ASSET | 1049 | 8.62 | 8.17 | 0.22 | 14.67 | 2.21 | 0.71 | 3.49 | |
Z SCORE | 988 | 16.91 | 9.23 | -2.57 | 71.93 | 20.72 | 1.48 | 4.30 | |
EFFICIENCY | 1051 | 65.02 | 63.72 | 41.85 | 101.10 | 13.76 | 0.59 | 3.23 | |
TIER1 | 1048 | 12.26 | 11.72 | 0.00 | 50.90 | 4.65 | 2.47 | 14.43 | |
NPLOANS | 1019 | 1.87 | 1.18 | 0.14 | 7.66 | 1.87 | 1.61 | 5.09 | |
LOANS_GR | 1041 | 5.04 | 3.80 | -15.10 | 30.61 | 11.29 | 0.39 | 2.93 | |
3.5 Depositors’ Reaction to EA Announcements
To test the second research hypothesis (H2), we investigate the effect of EA announcements on bank deposit growth using panel data fixed effect regression.15 Following the literature on bank deposit growth (i.e. Gilbert and Vaughan 2001; Finger and Hesse 2009) we control for bank specific and market variables,where the dependent variable is the deposit growth (DEPOSIT_GR) for the i-th bank at quarter t. Five specifications of the dependent variable are tested (TOTAL_DEP, SAVING_DEP, DEMAND_DEP, TIME_DEP, CORE_DEP). EVENT is a vector of j variables identifying the type of EA announcements (C&D_D, CMP_D, FA_D). BANK is a vector of k bank-specific variables (EFFICIENCY, Z SCORE, TOTAL ASSET, NPLOANS, LOANS_GR). MARKET is a vector of h market variables (GDP, S&P INDEX). Bank specific and market variables are collected from Bloomberg on a quarterly frequency.
$$ DEPOSIT\_{GR}_{i,t}=\alpha +{\sum}_1^j{\beta}_j{EVENT}_{i,j,t-1}+{\sum}_1^k{\gamma}_k{BANK}_{i,k,t-1}+{\sum}_1^h{\delta}_h{MARKET}_{h,t-1}+{\varepsilon}_{i,j} $$
(9)
Fixed effect panel data regression is used to account for any time-invariant unobserved characteristics and one quarter lag of all independent variables is used to control for endogeneity in the regression model.
To enable comparison between the sample of sanctioned (Tg) and non-sanctioned banks (Cg), we implement an OLS regression,where TYPE_D is a dummy variable equal to 1 for Tg and 0 for Cg; the other variables are similar to as in Eqn. (9). A detailed description of the variables is reported in Table 2.
$$ DEPOSIT\_{GR}_i=\alpha +\beta TYPE\_{D}_i+{\sum}_1^k{\gamma}_k{BANK}_{i,k}+{\sum}_1^h{\delta}_h{MARKET}_{i,h}+{\varepsilon}_{i,j} $$
(10)
4 Empirical Results
This section discusses the main results. Section 4.1 presents the results from the event study analysis. Section 4.2 reports the findings from the analysis of market reaction to EAs. Section 4.3 discusses the results on depositors’ reaction following EAs.
4.1 Results from Event Study Analysis
Table 3 presents the results from the event study analysis for banks that received EAs over the period 2004 to 2015. Cumulative average abnormal return (CAAR) is calculated across a range of event windows (7 days, 5 days, 3 days, 2 days and 1 day windows) and its significance is estimated across both parametric and non-parametric test statistics. Panel A reports CAAR across all events in the sample, while Panel B, Panel C and Panel D provide subsample analysis across the three types of events (C&D, CMP, FA respectively).
Table 3
Results from event study analysis
Parametric Test | Non Parametric Test | ||||||||
|---|---|---|---|---|---|---|---|---|---|
Rank Test | Sign test | ||||||||
CAAR Window | N | CAAR [t1 t2] | ZO | ZP | ZB | RT | RZ | SC | ST |
Panel A – All Events
| |||||||||
[-1,+5] | 1387 | -54.25** | -1.46 | -1.48 | -1.46 | -1.29 | -1.80 | -1.31 | -1.29 |
[-1,+3] | 1387 | -57.39** | -1.76 | -1.75 | -1.76 | -1.41 | -1.96 | -1.95 | -1.40 |
[-1,+1] | 1387 | -36.93* | -1.57 | -1.56 | -1.57 | -1.05 | -1.46 | -1.20 | -1.05 |
[0,+1] | 1387 | -25.08** | -1.30 | -1.30 | -1.30 | -1.25 | -1.74 | -1.46 | -1.24 |
[0] | 1387 | 12.16 | 0.84 | 0.84 | 0.84 | -0.73 | -1.02 | -0.75 | -0.73 |
Panel B – Cease & Desist Orders
| |||||||||
[-1,+5] | 504 | -124.59* | -1.61 | -1.54 | -1.61 | -1.51 | -1.06 | -0.83 | -1.51 |
[-1,+3] | 504 | -135.56** | -1.91 | -1.90 | -1.91 | -2.27 | -1.59 | -2.01 | -2.27 |
[-1,+1] | 504 | -76.49** | -1.82 | -1.81 | -1.82 | -2.07 | -1.45 | -1.88 | -2.07 |
[0,+1] | 504 | -26.63* | -0.82 | -0.81 | -0.82 | -1.02 | -0.72 | -1.33 | -1.02 |
[0] | 504 | 31.51 | 1.09 | 1.09 | 1.09 | -0.15 | -0.10 | -0.15 | -0.16 |
Panel C – Civil Money Penalty Orders
| |||||||||
[-1,+5] | 499 | -6.78 | -0.18 | -0.17 | -0.18 | -1.40 | -1.07 | -0.30 | -1.39 |
[-1,+3] | 499 | -32.02* | -0.91 | -0.91 | -0.91 | -1.71 | -1.31 | -0.82 | -1.70 |
[-1,+1] | 499 | -21.42* | -0.75 | -0.75 | -0.75 | -1.67 | -1.28 | -0.30 | -1.66 |
[0,+1] | 499 | -26.02** | -1.24 | -1.23 | -1.24 | -2.42 | -1.84 | -0.95 | -2.40 |
[0] | 499 | -4.80 | -0.34 | -0.34 | -0.34 | -1.39 | -1.06 | -0.18 | -1.37 |
Panel D – Formal Agreements
| |||||||||
[-1,+5] | 384 | -23.64* | -0.33 | -0.39 | -0.33 | -1.93 | -1.22 | -1.16 | -1.93 |
[-1,+3] | 384 | 12.22 | 0.22 | 0.22 | 0.22 | -0.54 | -0.34 | -0.47 | -0.54 |
[-1,+1] | 384 | -5.18 | -0.10 | -0.10 | -0.10 | 0.18 | 0.12 | 0.23 | 0.18 |
[0,+1] | 384 | -21.83 | -0.46 | -0.46 | -0.46 | -1.44 | -0.92 | -0.19 | -1.44 |
[0] | 384 | 8.82** | 0.29 | 0.29 | 0.29 | -2.41 | -1.52 | -1.02 | -2.40 |
Event study results show that CAAR is negative and significant when considering all events (Panel A) expect for the 1-day window, evidencing a significant and negative market reaction to EA announcements. However, the difference in market reaction becomes apparent when a sub-sample analysis is undertaken. Market reaction to C&D (Panel B) is negative and statistically significant across almost all the event windows analysed, indicating that equity markets react negatively following C&D announcement except on the day of the announcement. Market reaction to CMP (Panel C) is significant only for the 2-day, 3-day and 5-day event windows; while market reaction to FA (Panel D) is surprisingly positive and significant on the day of FA announcement.
In a nutshell, the market reacts negatively to C&D and CMP announcements, while weak or no reaction is found following FA announcements. This implies that the equity market is able to discriminate EAs based on the severity of the sanction, by penalizing banks for more severe sanctions, i.e. C&D and CMP, while reacting weakly for less severe sanction, i.e. FA. The magnitude of the coefficient, which represents the size of the reaction, is higher for C&D with respect to other event types, confirming market reacts the most following C&D announcements. FA announcements are expected to be not as severe compared to C&D and CMP. Moreover, FA announcements may also come as a relief for investors who would have been expecting a more negative sanction on the bank. Overall, the positive CAAR following the FA announcements may indicate investors’ relief that the bank is given a lenient sanction without the need to shut down its operations or incur additional financial penalty.
The results from the event study are in line with previous literature that documents a negative market reaction following EA announcements (Brous and Legett 1996; Jordan et al. 1999; Zeidan 2013). The subsample analysis extends previous studies by highlighting different market reactions across the three event types.
However, event study analysis does not allow for inferring causality between EA events and market reaction. To evaluate if the equity market reaction is due to EA announcements, we undertake a multivariate analysis and develop a control group based on PSM methodology (Section 3.2), making the analysis more robust and extending previous literature in this field.
4.2 Results from the Regression Models: Market Reaction to EAs
Tables 4 presents the results from the OLS regression model (Eqn.7) investigating market reaction to EA announcements for sanctioned banks. We regress bank-specific and market variables on cumulative abnormal returns (CAR) estimated for each sanctioned bank across four event windows (1 day [0], 2 days [0;+1], 3 days [-1;+1] and 5 days [-1;+3]).
Table 4
Regression results on market reaction to EAs
Dep.var.: CAR
| (1) | (2) | (3) | (4) |
|---|---|---|---|---|
CAR[0] | CAR[0,+1] | CAR[-1,+1] | CAR[-1,+3] | |
C&D_D
| 16.74 | -72.91 | -107.00* | -236.16** |
(38.784) | (55.411) | (62.707) | (96.407) | |
CMP_D
| -19.36 | -44.64 | -34.02 | -109.89 |
(35.404) | (46.238) | (52.093) | (69.343) | |
TOTAL ASSET
| -2.35 | 3.23 | 7.01 | 19.34* |
(5.244) | (7.587) | (8.182) | (11.284) | |
Z SCORE
| 0.38 | 0.89 | 0.91 | 0.39 |
(0.642) | (0.905) | (0.995) | (1.254) | |
EFFICIENCY
| 1.52 | -0.31 | -0.82 | -5.93 |
(1.287) | (1.729) | (1.958) | (3.677) | |
TIER1
| 0.51 | 3.55 | 3.95 | 12.46 |
(5.098) | (7.092) | (7.71) | (11.742) | |
S&P INDEX
| -140.02** | -78.26 | -94.78 | -209.32 |
(54.745) | (70.114) | (79.156) | (151.726) | |
PMI
| 2.8 | 6.96 | 8.69 | 20.64** |
(4.005) | (6.049) | (6.472) | (9.566) | |
SUBPRIME_D
| 70.92 | 81.84 | 44.78 | 54.27 |
(44.999) | (80.589) | (82.548) | (95.711) | |
GLOBAL_D
| 78.74* | 12.61 | 2.88 | 0.22 |
(41.753) | (66.383) | (71.095) | (78.36) | |
Constant
| -235.88 | -405.68 | -489.62 | -938.66* |
(249.969) | (368.737) | (389.235) | (533.363) | |
Adj. R-squared
| 1.74% | 0.82% | 1.23% | 3.53% |
Observations
| 1072 | 1072 | 1072 | 1072 |
The results from Table 4 highlight that the market reaction to C&D announcements is negative and statistically significant (for 3-day and 5-day event windows), while a negative but not statistically significant reaction is documented for other event types. These results are in line with the findings from the event study analysis (Table 3). Among control variables, TOTAL ASSET and PMI have a positive and significant coefficient for the 5 day event window. There is no significantly effect of the crisis periods (GLOBAL_D AND SUBPRIME_D) on the CARs indicating market reactions following EA announcements are not statistically different from other periods. Overall, results in Table 4 complement the findings from event study (Table 3) as well as extend previous studies in this field (Brous and Leggett 1996; Jordan et al. 1999; Zeidan 2013) by validating the findings through a test of causality.
These results confirm hypothesis H1: the equity market reacts negatively to EA announcements on US banks. In particular, the equity market is sensitive to C&D enforcement types and is able to discriminate EAs based on the severity of the sanction. Likewise, a weak or insignificant market reaction is found for the other event types. C&D orders are well recognized as the more serious formal enforcement action, taken when a bank’s prospects for failure are more than a remote possibility (Curry et al. 1999) and the above results are in line with our expectation. Moreover, a negative market reaction following C&D announcements suggests that more severe EAs are not fully anticipated by the market.
For banks receiving sanctions, the existence of different market reactions based on the type of sanction highlights the need to consequently adopt different behaviours, i.e. whether to react or not following a sanction announcement, along with realigning their communication strategy based on the type of sanction to minimize reputational loss. No differential market reaction during periods of financial crisis indicates the effect is not dependent on external economic climate. From banking supervisors and other policy makers’ perspectives, these results generate awareness of how the equity market would potentially react to different sanction announcements and would be relevant to guide further measures required when disclosing a formal EA. This would help to prevent panic among investors and other negative effects following EA announcements on banks and banks’ stakeholders.
In Table 5, as a robustness check, the sample is extended by introducing the non-sanctioned banks (Eqn. 8). In Panel A, the event dummies are replaced by the dummy TYPE_D that assumes value 1 for Tg and 0 for Cg. In Panel B, to obtain a more comprehensive understanding of how various types of events differ between treated and control group, we introduce interactions between TYPE_D and the sanctions type (TYPE*C&D and TYPE*CMP16). The results obtained from Table 4 are confirmed in Table 5. From Panel A, the main variable of interest, TYPE_D, is negative and statistically significant for the 1-day event window while not significant for others, suggesting that the market reacts negatively to EA announcements for sanctioned banks compared to the matched non-sanctioned banks, although the effect is short lived. Results from Panel B confirm equity market sensitivity following C&D announcements with respect to other event types.
Table 5
Regression results on market reaction to EAs – Tg and Cg
Dep.var.: CAR
| (1) | (2) | (3) | (4) |
|---|---|---|---|---|
CAR[0] | CAR[0,+1] | CAR[-1,+1] | CAR[-1,+3] | |
Panel A – OLS Regression
| ||||
TYPE_D
| -13.29** | -14.68 | -5.85 | 2.51 |
(6.527) | (9.918) | (12.189) | (15.597) | |
TOTAL ASSET
| -1.68 | -1.85 | -1.23 | 1.34 |
(1.525) | (2.339) | (2.747) | (3.651) | |
Z SCORE
| -0.25 | 0.08 | 0.29 | 0.13 |
(0.169) | (0.247) | (0.296) | (0.382) | |
EFFICIENCY
| -0.31 | -0.75* | -0.61 | -0.89 |
(0.261) | (0.411) | (0.505) | (0.65) | |
TIER1
| -0.13 | 1.65 | 2.33 | 1.64 |
(1.023) | (1.556) | (1.934) | (2.473) | |
S&P INDEX
| -34.55*** | -37.95** | -41.23* | -69.52** |
(11.675) | (18.038) | (22.176) | (28.035) | |
PMI
| 1.75** | 1.66 | 3.2** | 3.87** |
(0.801) | (1.224) | (1.506) | (1.909) | |
SUBPRIME_D
| 25.03* | 18.14 | 9.84 | 14.04 |
(13.623) | (20.442) | (24.583) | (30.962) | |
GLOBAL_D
| 23.09** | 11.88 | 6.87 | 12.36 |
(9.145) | (13.583) | (16.905) | (21.847) | |
Constant
| -43.44 | -43.84 | -164.39 | -205.24 |
(53.679) | (81.489) | (100.522) | (127.771) | |
Adj. R-squared
| 1.34% | 0.88% | 0.83% | 0.77% |
Observations
| 1958 | 1958 | 1958 | 1958 |
Panel B – OLS Regression with interactions
| ||||
TYPE*C&D
| 19.23 | -21.96 | -43.54* | -65.87** |
(12.67) | (19.389) | (23.667) | (29.84) | |
TYPE*CMP
| 1.6 | -7.24 | -5.73 | -27.5 |
(11.994) | (18.091) | (22.707) | (29.213) | |
TOTAL ASSET
| -0.48 | -0.38 | 2.26 | 9.46* |
(2.156) | (3.5) | (4.119) | (5.485) | |
Z SCORE
| -0.04 | 0.49 | 0.99** | 0.55 |
(0.264) | (0.382) | (0.46) | (0.589) | |
EFFICIENCY
| -0.23 | -0.87 | -0.7 | -1.66* |
(0.375) | (0.589) | (0.716) | (0.895) | |
TIER1
| -0.35 | 1.62 | 3.51 | 2.07 |
(1.546) | (2.34) | (2.964) | (3.846) | |
S&P INDEX
| -44.82*** | -40.9 | -46.4 | -71.06* |
(17.204) | (26.888) | (33.353) | (41.275) | |
PMI
| 1.88 | 1.06 | 2.09 | 2.7 |
(1.192) | (1.844) | (2.277) | (2.862) | |
SUBPRIME_D
| 37.09* | 20.92 | 6.78 | -4.57 |
(21.041) | (30.874) | (37.12) | (47.6) | |
GLOBAL_D
| 25.78* | 2.38 | -9.39 | -10.49 |
(13.861) | (20.687) | (26) | (33.636) | |
Constant
| -86.67 | -22.85 | -136.81 | -129.14 |
(82.278) | (125.87) | (155.708) | (197.153) | |
Adj. R-squared
| 1.93% | 1.51% | 2.36% | 2.50% |
Observations
| 971 | 971 | 971 | 971 |
4.3 Results from the Regression Models: Depositors’ Reaction to EAs
Table 6 reports results from the regression model in Eqn. (9) assessing depositors’ reaction following EA announcements for the sample of sanctioned banks. A fixed effect panel data regression is used to ascertain if depositors react to EA announcements. To this purpose, different measures of deposit growth are considered: growth in total deposits (Table 6, column 1), growth in saving deposits (Table 6, column 2), growth in demand deposits (Table 6, column 3), growth in time deposits (Table 6, column 4) and growth in core deposits (Table 6, column 5). The difference in the types of deposits provides an indication of the reaction associated with the type of depositor at the sanctioned bank.
Table 6
Regression results on depositors’ reaction to EAs
Dep.var.:DEPOSIT_GR
| (1) | (2) | (3) | (4) | (5) |
|---|---|---|---|---|---|
TOTAL_DEP | SAVING_DEP | DEMAND_DEP | TIME_DEP | CORE_DEP | |
C&D_D
| 0.97* | 0.68 | -1.95*** | 0.86 | 2.54** |
(0.528) | (0.905) | (0.699) | (0.767) | (0.996) | |
CMP_D
| 1.13** | -0.55 | 0.57 | 0.70 | 2.66** |
(0.478) | (0.735) | (0.634) | (0.681) | (1.033) | |
FA_D
| 1.64*** | 3.36*** | 1.10 | 2.23** | 1.57 |
(0.579) | (0.84) | (0.89) | (0.886) | (1.056) | |
EFFICIENCY
| 0.01 | -0.02* | 0.06*** | -0.01 | -0.08*** |
(0.007) | (0.012) | (0.01) | (0.01) | (0.015) | |
Z SCORE
| -0.03*** | -0.05*** | -0.06*** | -0.04*** | -0.01 |
(0.004) | (0.006) | (0.005) | (0.005) | (0.008) | |
TOTAL ASSET
| -0.46** | 1.39*** | 6.51*** | -1.40*** | -9.12*** |
(0.201) | (0.353) | (0.393) | (0.369) | (0.52) | |
NPLOANS
| 0.27*** | 1.48*** | 1.45*** | 1.16*** | -0.97*** |
(0.064) | (0.121) | (0.102) | (0.1) | (0.152) | |
LOANS_GR
| 0.58*** | 0.50*** | 0.45*** | 0.53*** | 0.79*** |
(0.007) | (0.011) | (0.01) | (0.012) | (0.019) | |
GDP
| -1.09*** | -1.87*** | -2.31*** | -1.69*** | 1.06*** |
(0.133) | (0.188) | (0.185) | (0.18) | (0.304) | |
S&P INDEX
| 0.02 | 0.34*** | 0.93*** | 0.20*** | -0.76*** |
(0.029) | (0.051) | (0.042) | (0.042) | (0.055) | |
Constant
| 8.00*** | -6.33** | -54.74*** | 16.55*** | 82.90*** |
(1.791) | (2.937) | (3.479) | (3.34) | (4.675) | |
Adj. R-square
| 34.45% | 13.45% | 18.30% | 16.79% | 25.96% |
Observations
| 37710 | 36375 | 37084 | 36681 | 36862 |
From Table 6, considering the growth in all types of deposits collectively, the quarters following C&D, CMP and FA announcements show a significant increase in bank deposits. To provide a more accurate interpretation of this result, it is important to distinguish the reaction based on the type of sanction and the type of deposits, as depositors could exhibit a different behaviour following a particular EA.
Looking at demand deposits (Table 6, column 3), a negative and highly significant coefficient for C&D_D indicates demand deposits holders reduce their deposits in sanctioned banks in quarters following C&D announcements. However, no such effect can be observed for quarters following CMP and FA announcements. Demand depositors have the liberty to move their deposits without incurring any financial penalty and the reduction in deposits may indicate depositors disciplining their banks following a severe sanction announcement (Gilbert and Vaughan 2001). A positive and significant coefficient is found for savings deposits following FA_D announcements (Table 6, column 2) and following C&D_D and CMP_D announcements for core deposits (Table 6, column 5). This set of results confirm our hypothesis H2 but only for C&D_D in case of demand deposits and are in line with previous literature expecting depositors to respond unfavourably to EAs by panicking and withdrawing funds from their sanctioned bank, i.e. depositor disciplining mechanism (i.e. Gilbert and Vaughan 2001; Davenport and McDill, 2006; Semenova 2007). However, H2 is not confirmed across the remaining measures of deposit growth.
In fact, when considering growth in core deposits (Table 6, column 5), the coefficients for C&D_D and CMP_D are positive and significant, indicating an apparent positive attitude towards the sanctioned banks. This could be attributed to a possible strategy adopted by the sanctioned bank following an EA announcement, i.e. either the sanctioned banks increase the interest offering to attract more core depositors to compensate for the (anticipated) negative market reaction or current depositors expect their sanctioned banks to offer better risk-adjusted returns in terms of higher interest rates and hence the anticipated growth. In support of this, previous literature has shown that deposit holders at thrift institutions respond to increases in the probability of bank failure by demanding higher returns (Park and Peristiani 1998). An alternative explanation for the positive C&D_D and CMP_D coefficient for core deposits is explained in Gilbert and Vaughan (2001), where borrowers could interpret C&D announcement as a signal that the bank has loose credit standards and flood it with increased loan demand, causing sanctioned banks to attract additional deposits to fund new loans, causing a rise in deposit levels.
The positive and significant coefficient for FA_D (Table 6, columns 1, 2 and 4) when considering growth in total, saving and time deposits can be explained in the context of FA sanctions, which are less severe compared to the other two types of sanctions. Depositors may consider FA announcement as more of a corrective action on their bank without the need to cease existing operations or incur financial penalty. Consequently, following an FA announcement, depositors consider their bank to be more sound and hence the potential increase in deposits for the sanctioned banks. This result corroborates our findings in Table 3 (event study analysis) showing positive market reaction, due to depositors expecting FA announcement to be a corrective mechanism.
These results show that the announcement of EAs by bank regulators which is circulated by media represents an important source of information for depositors to form a perception and consequently alter their deposit accounts at the sanctioned banks.
In Table 7, as a robustness check, we undertake a comparative analysis between Tg and Cg (Eqn. 10). In Panel A, the event dummies are replaced by the dummy TYPE_D that assumes value 1 for Tg and 0 for Cg. In Panel B, we introduce interactions between TYPE_D and the sanctions type (TYPE*C&D and TYPE*CMP).17 The results obtained from Table 7 corroborate the findings in Table 6. From Panel A, the coefficient for TYPE_D is positive and significant for growth in total and core deposits while negative and significant for growth in demand deposits. The results indicate a positive growth in total and core deposits and a negative growth in demand deposits for one quarter following the EA announcement for sanctioned bank in comparison to a similar matched non-sanctioned bank when all EAs are considered collectively. Results from Panel B, partially supports the above findings. For sanctioned banks following C&D and CMP announcements, there is negative growth in demand and saving deposits; however these dummy variables lose significance for core deposits, indicating the relationship is not statistically significant when looked at the core deposits growth for sanctioned banks. As a further robustness check to ensure the reliability of the results, the two-quarter lead of deposit growth is used to test if the effect on deposit growth is persistent over two subsequent quarters. The results not reported here are consistent to those in Tables 6 and 7.
Table 7
Regression results on depositors’ reaction to EAs – Tg and Cg
Dep.var.: DEPOSIT_GR
| (1) | (2) | (3) | (4) | (5) |
|---|---|---|---|---|---|
TOTAL_DEP | SAVING_DEP | DEMAND_DEP | TIME_DEP | CORE_DEP | |
Panel A – OLS Regression
| |||||
TYPE_D
| 0.96*** | 1.02 | -1.32** | 0.59 | 2.01** |
(0.361) | (0.695) | (0.619) | (0.589) | (0.806) | |
EFFICIENCY
| -0.01 | -0.13*** | 0.003 | -0.01 | 0.001 |
(0.017) | (0.031) | (0.027) | (0.027) | (0.033) | |
Z SCORE
| -0.06*** | -0.11*** | -0.08*** | -0.08*** | -0.06*** |
(0.009) | (0.018) | (0.016) | (0.015) | (0.021) | |
TOTAL ASSET
| 0.25*** | -0.04 | 0.86*** | 0.97*** | -0.4* |
(0.087) | (0.173) | (0.175) | (0.169) | (0.207) | |
NPLOANS
| 0.06 | 0.37 | 0.65*** | 0.06 | -0.07 |
(0.13) | (0.244) | (0.218) | (0.21) | (0.276) | |
LOANS_GR
| 0.6*** | 0.44*** | 0.52*** | 0.43*** | 0.88*** |
(0.021) | (0.038) | (0.034) | (0.038) | (0.043) | |
GDP
| 0.01 | 0.61*** | 0.86*** | -0.08 | -0.77*** |
(0.079) | (0.149) | (0.129) | (0.124) | (0.165) | |
S&P INDEX
| 1.88*** | 0.96 | -0.66 | 1.86** | 1.89 |
(0.556) | (1.069) | (0.955) | (0.932) | (1.195) | |
Constant
| 3.4** | 16.05*** | 0.56 | -0.74 | 2.02 |
(1.455) | (2.944) | (2.586) | (2.524) | (3.123) | |
Adj. R-square
| 43.47% | 12.63% | 17.88% | 15.17% | 26.32% |
Observations
| 1908 | 1817 | 1830 | 1833 | 1847 |
Panel B – OLS regressions with interaction
| |||||
TYPE*C&D
| -0.47 | -3.85*** | -3.5*** | -0.44 | 1.51 |
(0.66) | (1.264) | (1.121) | (1.129) | (1.39) | |
TYPE*CMP
| -1.05* | -4.73*** | -2.43** | -1.09 | 1.63 |
(0.615) | (1.207) | (1.087) | (1.07) | (1.449) | |
EFFICIENCY
| -0.04* | -0.14*** | -0.08** | -0.08** | 0.003 |
(0.023) | (0.042) | (0.036) | (0.036) | (0.044) | |
Z SCORE
| -0.07*** | -0.14*** | -0.05** | -0.08*** | -0.05* |
(0.014) | (0.027) | (0.025) | (0.024) | (0.029) | |
TOTAL ASSET
| 0.14 | 0.49* | 0.74*** | 0.59** | -0.67** |
(0.125) | (0.254) | (0.247) | (0.234) | (0.287) | |
NPLOANS
| 0.25 | 0.15 | 0.55* | 0.53* | 0.86** |
(0.179) | (0.335) | (0.284) | (0.3) | (0.351) | |
LOANS_GR
| 0.63*** | 0.47*** | 0.47*** | 0.5*** | 0.99*** |
(0.03) | (0.053) | (0.049) | (0.055) | (0.055) | |
GDP
| -0.02 | 0.69*** | 0.97*** | -0.04 | -0.75*** |
(0.115) | (0.21) | (0.178) | (0.193) | (0.238) | |
S&P INDEX
| 2.27*** | 1.05 | 0.14 | 1.82 | 2.01 |
(0.844) | (1.535) | (1.341) | (1.402) | (1.699) | |
Constant
| 7.2*** | 16.74*** | 7.09** | 6.35* | 2.6 |
(2.006) | (4.239) | (3.531) | (3.585) | (4.504) | |
Adj. R-square
| 44.64% | 17.11% | 19.13% | 16.74% | 28.83% |
Observations
| 937 | 897 | 906 | 875 | 919 |
Overall, the above results indicate that EA announcements could cause a positive or negative growth in bank deposits depending on the type of deposit and the type of EA being considered. In particular, savings and demand deposits show significant negative effects for sanctioned firms following C&D and CMP announcements.
These results could be interpreted from two different points of view. On one hand, the absence of negative effects following EA announcements could highlight a need for increasing depositor’s awareness. On the other hand, it shows supervisory action meets its purpose of reducing the risk of bank runs. Consequently, any policy initiative related to EA announcements should consider the balance between increasing depositors’ awareness and avoiding bank runs.
5 Conclusion
This study investigates market movement and depositors’ reaction following EA announcements on US banking institutions over the period 2004-2015. We complement previous literature by providing new empirical evidence across a range of EAs types and deposits. We employ event study and multivariate analyses on a wide dataset of US banks EAs to test the causal relationship of EAs on equity markets and depositors. We build a manually collected dataset of EA announcements by US supervisory authorities and validate the findings by identifying a sample of comparable non-sanctioned banks using PSM methodology. To the best of our knowledge, this is the first study that provides an in depth analysis of how key bank stakeholders, i.e. shareholders and depositors, react to US banks EAs.
Our results suggest equity market is able to discriminate EAs based on the severity of the sanction, by penalizing banks for more severe sanctions (C&D), while reacting weakly for other sanctions (CMP and FA). A reduction in deposit growth is found for demand deposits and saving deposits following C&D and CMP announcements, in line with previous literature expecting depositors to panic and withdraw funds from their sanctioned bank, while core depositors seem to reward sanctioned banks for a higher return following EA announcements. Following FA announcements, depositors tend to increase their deposits considering FA to be a less severe sanction and more of a corrective mechanism.
Equity market and depositors’ reaction following EA announcements expand the existing knowledge on the consequences of banking supervision. Indeed, the existence of different market reactions based on the type of sanction highlights the need for banks to consequently adopt different behaviour, i.e. deciding to react or not following a sanction announcement, along with realigning their communication strategy based on the type of sanction to minimize reputational loss. The existence of different depositors’ reaction based on the type of deposit (and sanction) suggests that banks should manage their relationship with depositors depending on the deposit (and sanction) type, i.e. considering demand depositors are willing to reduce their deposits following C&D announcements, while core depositors are willing to keep the funds for a higher return. From banking supervisors and policy makers’ perspective, results from this study generate a better understanding of how supervisory enforcements affect shareholders and depositors. This could be relevant to deduce and guide further policy measures required when disclosing a formal EA and to enhance supervisory effectiveness. This would be important to help prevent panic among investors and depositors as well as other negative effects on banks and their stakeholders following an EA announcement.
Acknowledgements
We would like to thank the Editor, the special issue co-Editor and the anonymous reviewers for their valuable comments and constructive suggestions. We are also grateful to the participants of the 6th International Conference of the Financial Engineering and Banking Society (FEBS) held at the University of Malaga, Spain, in June 2016.
Open Access This article is distributed under the terms of the Creative Commons Attribution 4.0 International License (http://creativecommons.org/licenses/by/4.0/), which permits unrestricted use, distribution, and reproduction in any medium, provided you give appropriate credit to the original author(s) and the source, provide a link to the Creative Commons license, and indicate if changes were made.
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