See discussions, stats, and author profiles for this publication at: https://www.researchgate.net/publication/225977276 Did Good Corporate Governance Improve Bank Performance during the Financial Crisis? Article in Journal of Financial Services Research · April 2012 DOI: 10.1007/s10693-011-0108-9 CITATIONS READS 111 4,105 2 authors, including: Sami Vähämaa University of Vaasa 51 PUBLICATIONS 1,175 CITATIONS SEE PROFILE All content following this page was uploaded by Sami Vähämaa on 16 May 2014. The user has requested enhancement of the downloaded file. Forthcoming in Journal of Financial Services Research The final publication is available at springerlink.com: http://dx.doi.org/10.1007/s10693-011-0108-9 DID GOOD CORPORATE GOVERNANCE IMPROVE BANK PERFORMANCE DURING THE FINANCIAL CRISIS? Emilia Peni a,b,*, Sami Vähämaa a,b,** a University of Vaasa, Department of Accounting and Finance b University of Central Florida, Department of Finance First Draft: August 2009 This Draft: March 2011 Abstract This paper focuses on the effects of corporate governance on bank performance during the financial crisis of 2008. Using data on large publicly traded U.S. banks, we examine whether banks with stronger corporate governance mechanisms were associated with higher profitability and better stock market performance amidst the crisis. Our empirical findings on the effects of corporate governance on bank performance are mixed. Although the results suggest that banks with stronger corporate governance mechanisms were associated with higher profitability in 2008, our findings also indicate that strong governance may have had negative effects on stock market valuations of banks amidst the crisis. Nevertheless, we document that banks with strong corporate governance practices had substantially higher stock returns in the aftermath of the market meltdown, indicating that good governance may have mitigated the adverse influence of the crisis on bank credibility. JEL classification: G01, G21, G30 Keywords: corporate governance; bank performance; financial crisis We wish to thank an anonymous referee, Stanley D. Smith, James E. McNulty, and participants at the 2010 Eastern Finance Association Meeting for insightful comments and discussions. The authors gratefully acknowledge the financial support of the Foundation for Economic Education and the NASDAQ OMX Nordic Foundation. Emilia Peni further acknowledges the support of the Evald and Hilda Nissi Foundation, the Fulbright Center, and the South Ostrobothnia Fund of the Finnish Cultural Foundation, and Sami Vähämaa is grateful for the support of the Finnish Foundation for Advancement of Securities Markets, the Emil Aaltonen Foundation, and the Paulo Foundation. * Address: University of Vaasa, Department of Accounting and Finance, P.O. Box 700, FI-65101 Vaasa, Finland; Tel:. +358 6 324 8547; E-mail address: [email protected] ** Corresponding author. Address: University of Vaasa, Department of Accounting and Finance, P.O. Box 700, FI65101 Vaasa, Finland; Tel.: +358 6 324 8197; E-mail address: [email protected] 1 1. INTRODUCTION The financial crisis of 2008 is to a large extent attributable to excessive risk-taking by banks. Given that corporate governance is essentially a mechanism for addressing agency problems and controlling risk within the firm, it is not surprising that the recent initiatives and statements by banking supervisors, central banks, and other authorities have emphasized the importance of effective corporate governance practices in the banking sector (see e.g., Basel Committee on Banking Supervision 2010; Board of Governors of the Federal Reserve System 2010a-b; OECD 2010). Thus, it is now widely acknowledged that shortcomings in bank corporate governance may have had a central role in the development of the crisis. In this paper, we aim to provide empirical evidence on the effects of corporate governance on bank performance during the financial crisis. In particular, we use data on large publicly-traded U.S. banks to examine whether banks with strong governance were associated with higher profitability and better stock market performance amidst the crisis. Previously, an extensive empirical literature has documented that firms with strong corporate governance mechanisms are generally associated with better financial performance, higher firm valuation and higher stock returns (see e.g., Ammann et al. 2011; Bebchuk et al. 2009; Bhagat and Bolton 2008; Brown and Caylor 2006, 2009; Chhaochharia and Laeven 2009; Core et al. 2006; Cremers and Ferrell 2010; Cremers and Nair 2005; Gompers et al. 2003; Johnson et al. 2009; Renders et al. 2010). The role of corporate governance in the banking industry has been examined e.g. in Caprio et al. (2007), Cornett et al. (2009), de Andres and Vallelado (2008), Hanazaki and Horiuchi (2003), Jiraporn and Chintrakarn (2009), Laeven and Levine (2009), Macey and O’Hara (2003), Mishra and Nielsen (2000), Pacini et al. (2005), 2 Sierra et al. (2006), and Webb Cooper (2009). Consistent with the literature on non-financial firms, these studies demonstrate that strong corporate governance has positive effects on the financial performance and stock market valuation of banks. More generally, the prior studies indicate that the same corporate governance attributes that affect non-financial firms are also relevant in bank governance. Given the existing empirical evidence on the positive influence of good governance on bank performance, we hypothesize in this paper that the strength of corporate governance is reflected in bank performance during the financial crisis. Specifically, we posit that banks with stronger corporate governance mechanisms had (i) higher profitability, (ii) higher market valuations, and (iii) less negative stock returns amidst the crisis. Nevertheless, it is also possible that the link between good corporate governance and bank performance documented in the prior literature is related to higher levels of risk-taking, in which case strong governance may lead to poor performance during periods of market turmoil. The relationship between corporate governance and bank risk-taking has been recently examined in Akhigbe and Martin (2008), Fortin et al. (2010), and Pathan (2009). While Akhigbe and Martin (2008) document that risk measures of financial firms vary inversely with the strength of corporate governance, the findings of Pathan (2009) and Fortin et al. (2010) suggest that banks with strong governance attributes may take more risk. This paper is not the first to examine bank performance during the financial crisis. Beltratti and Stulz (2010) focus on bank stock returns in 31 countries over the period from July 2007 to December 2008, and document that large banks with lower leverage ratios had less negative stock returns during the crisis. Interestingly, their results also suggest that banking regulation differences across countries are not related to bank performance. Regarding corporate 3 governance attributes, Beltratti and Stulz (2010) find that banks with strong, shareholderfriendly boards performed worse amidst the market turmoil. Erkens et al. (2010) examine the influence of board independence and institutional ownership on bank stock returns in 30 countries from January 2007 to September 2008. Their results indicate that banks with more independent boards and larger institutional ownership had lower stock returns during the crisis. Moreover, Erkens et al. (2010) document a positive relationship between institutional ownership and bank risk-taking at the onset of the crisis. Finally, Fahlenbrach and Stulz (2011) investigate the effects of chief executive officer (CEO) ownership and compensation incentives on the stock returns and profitability of U.S. banks. They find that banks whose managers have larger equity ownership were associated with lower stock returns and profitability in 2008. Although flaws in managerial compensation incentives are often considered among the factors contributing to the development of the financial crisis, the results documented in Fahlenbrach and Stulz (2011) suggest that the CEO’s option compensation and cash bonuses are unrelated to bank performance amidst the crisis. In this paper, we use data on 62 large, publicly traded U.S. commercial banks to empirically examine the association between corporate governance and bank performance during the financial crisis. We apply the Gov-Score governance index of Brown and Caylor (2006, 2009) to measure the strength of governance mechanisms within banks, and analyze the effects of corporate governance on bank profitability, market valuation, and stock returns. Our main findings can be summarized as follows. First, consistent with our research hypothesis, we find that banks with stronger corporate governance mechanisms had significantly higher profitability in 2008. This finding suggests that good governance may have moderated the adverse influence of the financial crisis on financial performance. Second, our results indicate 4 that strong corporate governance practices may have had negative effects on stock market valuations of banks during the crisis, as banks with stronger governance are found to be associated with lower Tobin’s Qs and stock returns amidst the crisis. Thus, inconsistent with our hypothesis, the empirical findings suggest that good corporate governance did not create shareholder value in the banking industry during the market turmoil. Nevertheless, we also find that banks with stronger corporate governance mechanisms provided substantially higher stock returns in the immediate aftermath of the crisis from March 2009 onwards, indicating that good governance may have mitigated the adverse effects of the financial crisis on bank credibility among stock market participants. The remainder of this paper proceeds as follows. The second section describes the data set on large publicly traded U.S. banks. The third section presents the methodology and reports the empirical findings on the association between corporate governance and bank performance during the financial crisis. Finally, the last section provides concluding remarks. 2. DATA The data used in our empirical analysis consist of the large, publicly traded U.S. commercial banks that are included in the S&P 1500 index. After eliminating the banks with insufficient financial and/or corporate governance information, we obtain a sample comprising of 62 individual banks and 248 firm-year observations for the fiscal years 2005–2008. The banks included in our sample are listed in Appendix 1. Despite the relatively small number of individual banks, the sum of total assets of these banks totalled about $8.6 trillion at the end of 2008, and thereby the sample covers a substantial proportion of the total amount of banking 5 assets in the U.S. Our empirical analysis requires data on the banks’ (i) corporate governance structures, (ii) financial statements, and (iii) stock prices. The corporate governance data used in the analysis are obtained from Georgia State University, while the income statement and balance sheet items are collected from Thomson Reuters Worldscope. The data on stock prices and market capitalizations of banks are obtained from CRSP. We apply the Gov-Score corporate governance index developed by Brown and Caylor (2006, 2009) to measure the strength of governance. The Gov-Score index is based on 51 different firm-specific governance attributes, which present both internal and external governance of the firm. The different governance sectors considered in the Gov-Score are auditing, board of directors, charter/bylaws, director education, executive and director compensation, ownership, progressive practices, and state of incorporation (for a detailed discussion, see Brown and Caylor, 2006). Each of the considered individual corporate governance attributes is given either a value of one or zero based on whether the governance factor is at the minimally acceptable level or above it. The Gov-Score is then calculated as the sum of the values of individual governance attributes, and may thus take values between zero and 51, with higher values of the index corresponding to stronger corporate governance practices. Given that the prior literature (see e.g., Black et al. 2006, Cremers and Ferrell 2010) has suggested that corporate governance structures change slowly and the implications of the governance practices can be seen with a lag, we use the Gov-Scores for year 2005 in our empirical analysis. Hence, we assume in our analysis that the strength of corporate governance can be quantified with the Gov-Score index, and moreover, that the strength of governance mechanism incorporated in 2005 is reflected in bank performance during 2005–2008. 6 Considerable empirical evidence suggests that strong corporate governance has positive effects on the firm’s financial performance, market valuation, and stock returns (see e.g., Ammann et al. 2011; Bebchuk et al. 2009; Bhagat and Bolton 2008; Brown and Caylor 2006, 2009; Chhaochharia and Laeven 2009; Cremers and Ferrell 2010; Gompers et al. 2003; Johnson et al. 2009; Renders et al. 2010). Following the prior bank performance literature (e.g., Caprio et al. 2007; Chiorazzo et al. 2008; Ciciretti et al. 2009; de Andres and Vallelado 2008; Outreville 2010; Sierra et al. 2006), we employ return on assets (ROA) and Tobin’s Q to measure the financial performance and market valuation of banks. We calculate return on assets as the earnings before interest and taxes divided by the book value of total assets. Tobin’s Q is computed as the sum of market value of equity and the book value of liabilities divided by the book value of total assets. In addition, we also calculate stock returns for three distinct subperiods between March 2007 and December 2009 in order to examine the effects of corporate governance on stock market performance during the financial crisis. We employ several control variables to account for the potentially confounding effects of bank-specific characteristics such as size, leverage, and risk on profitability and market valuation. The control variables used in our main regressions are: (i) bank size (SIZE) which is measured by the logarithm of the bank’s total assets, (ii) leverage (LEV) which is defined as the ratio of total liabilities to total assets, (iii) the amount of lending activities (LOANTA) which is measured by ratio of total lending to total assets, (iv) stock return volatility (VOLA) which is calculated as the annualized standard deviation of monthly stock returns, and (v) a dummy variable (LOSS) that equals one for banks that report negative earnings during the fiscal year. (insert Table 1 about here) 7 Table 1 reports the descriptive statistics of the data used in the main analysis. The descriptive statistics are reported separately (i) for the complete sample of 248 firm-year observations, (ii) for the crisis year 2008, (iii) for banks with stronger corporate governance mechanisms, and (iv) for banks with weaker corporate governance. The stronger governance subsample consists of banks with above median Gov-Scores (GOV 33) and the weaker governance subsample consists of banks with below median Gov-Scores (GOV 32). The table also reports p-values for two-tailed t-tests and Wilcoxon rank-sum tests of the null hypothesis that there is no difference between the stronger and weaker governance subsamples. As can be noted from the table, the Gov-Scores of the banks included in the sample range from 24 to 40 with a mean governance score of 31.44. Bank profitability, as measured by ROA, varies between –6.08 and 5.11 percent, with a mean of 1.91 percent. The mean ROA of 0.31 percent in 2008 demonstrates the vast decline in bank profitability during the financial turmoil. The means and medians for the stronger and weaker governance subsamples indicate that banks with stronger corporate governance mechanisms have significantly higher profitability, suggesting that strong governance may improve bank performance. Tobin’s Q, our measure of market valuation, has a mean value of 1.06 and ranges from 0.91 to 1.28. It should also be noted that both the mean and the median Qs are below one in 2008 amidst the meltdown of financial markets. In a univariate setting, a t-test and the Wilcoxon rank-sum test suggest that there is no difference in market valuation between the stronger and weaker governance subsamples. Although our sample consists of the largest banks in the U.S., the banks included in the sample are heterogeneous in terms of size. The logarithm of total assets (SIZE) varies from 7.15 (i.e., $1.27 billion) to 14.60 ($2.18 trillion). The subsample descriptive statistics and comparison tests indicate that banks with stronger corporate governance tend to be significantly larger than 8 banks with weaker governance mechanisms. The mean leverage ratio (LEV) is 0.90 and ranges from 0.73 to 0.98. There is no statistically significant difference in financial leverage between the stronger and weaker governance subsamples. Our sample represents a diverse range of lending activity with the proportion of total loans to total assets (LOANTA) varying between 16.54 and 93.65 percent. Interestingly, both the mean and the median LOANTA figures suggest that the banks with stronger corporate governance structures are associated with a lower amount of lending. The annualized stock return volatility (VOLA) has a mean of 28.20 percent during the sample period. Not surprisingly, Table 1 demonstrates that the volatility of bank stocks was extremely high in 2008, with a mean estimate of 57.24 percent. The mean and the median volatility estimates indicate that the banks with stronger corporate governance have lower stock return volatility, albeit the difference in means is not statistically significant. Finally, the reported statistics for the LOSS dummy variable suggest that there is no difference between the stronger and weaker governance subsamples in the likelihood to report losses. (insert Table 2 about here) Table 2 presents the pairwise correlations between the variables used in the analysis. Our test variable GOV is strongly positively correlated with bank size and negatively correlated with loans to total assets (LOANTA) and stock return volatility (VOLA). Thus, consistent with the prior literature and Table 1, the correlations indicate that larger banks tend to have stronger governance structures. The correlations between GOV and the performance measures ROA (0.067) and Tobin’s Q (–0.049) are insignificant. As expected, our dependent variables ROA and 9 Q are positively correlated with each other. Furthermore, Table 2 suggests that both bank performance measures are strongly negatively correlated with VOLA and LOSS which, in turn, exhibit a strong positive correlation with each other. Finally, based on the correlations, the proportion of loans to total assets seems to decrease with bank size. 3. CORPORATE GOVERNANCE AND BANK PERFORMANCE 3.1. Financial performance and market valuation To examine the effects of corporate governance on bank performance during the financial crisis, we estimate alternative versions of the following panel regression specification: PERF j , t 1 GOV j ,t 2 GOV j ,t YEAR 2008 j 3 SIZE j ,t 4 LEV j , t (1) 2008 5 LOANTA j ,t 6 VOLA j , t 7 LOSS j ,t y YEAR jy j ,t y 2006 where PERFj,t denotes one of the alternative performance measures (ROA or Tobin’s Q) for bank j at time t, GOVj,t is the Gov-Score of Brown and Caylor (2006, 2009), SIZEj,t is the logarithm of total assets, LEVj,t is financial leverage measured as the ratio of total liabilities to total assets, LOANTAj,t is loans to total assets, VOLAj,t is the logarithm of annualized volatility of stock returns, LOSSj,t is a dummy variable that equals one for banks that report negative earnings during year t, and YEARjy is a dummy variable for fiscal years controlling for the possible change in bank performance over time. Throughout the panel regressions, we use standard errors that are corrected for clustering at the bank level. 10 Table 3 reports the estimation results of alternative versions of Equation (1) with ROA as the dependent variable. Models (1) and (2) are parsimonious versions of Equation (1) that include only two control variables (SIZE and LEV) and year fixed-effects. The estimated coefficients for GOV are positive and statistically significant at the 5 percent level in both regression specifications, thereby suggesting that strong corporate governance mechanisms improve bank profitability. More importantly, consistent with our hypothesis, the coefficient for the interaction variable GOV×YEAR2008 is positive and statistically highly significant, indicating that strong governance had a positive effect on bank performance during the financial crisis. The estimates also suggest that bank profitability decreases with increasing leverage (LEV) and, as expected, that profitability was severely affected by the crisis in 2008 (YEAR2008). It can be further noted from the table that both model specifications have relatively good explanatory power for bank profitability with adjusted R2s of about 37 percent. (insert Table 3 about here) Models (3) and (4) include the full set of bank-specific control variables. The adjusted R2s of these regressions are about 65 percent, and the F-statistics are significant at the 1 percent level, indicating a good fit of the models. Again, the coefficient estimates for GOV are positive and statistically significant, and also the coefficient for the interaction variable GOV×YEAR2008 is positive and highly significant. Therefore, consistent with our hypothesis, the estimates indicate that good corporate governance generally improves bank performance, and moreover, that the positive effect of good governance on profitability was particularly strong in 2008. These results indicate that strong internal corporate governance mechanisms within banks may 11 have moderated the adverse effects of the financial crisis on bank performance. As can be further noted from Table 3, profitability of banks is negatively associated with leverage (LEV) and the proportion of total loans to total assets (LOANTA). The highly significant negative coefficients for the YEAR2008 dummy variable yet again demonstrate the substantial impact of the financial crisis on bank performance. Table 4 presents the regression results for the effects of corporate governance on Tobin’s Q. Similar to Table 3, we first estimate reduced versions of Equation (1) with only two control variables and year fixed-effects (Models 1 and 2). Consistent with the prior literature (see e.g., Ammann et al. 2011; Brown and Caylor 2006; Cremers and Ferrell 2010; Gompers et al. 2003; Johnson et al. 2009), our estimates indicate that the strength of corporate governance is positively associated with market valuations, as the coefficient estimates for GOV are positive and statistically significant in both regression specifications. Interestingly, however, the coefficient for the interaction variable GOV×YEAR2008 is negative and statistically significant at the 1 percent level, thereby suggesting that strong corporate governance mechanisms may have reduced the market valuation of banks in the midst of the financial crisis. The estimated coefficients for the control variables are highly significant, thus indicating that market valuation decreases with bank size (SIZE) and increases with leverage (LEV). The F-statistics of both regression specifications are significant at the 1 percent level and the adjusted R2s are about 42 percent. (insert Table 4 about here) 12 The full set of control variables is included in Models (3) and (4). As can be noted from Table 4, the estimated coefficient for GOV is positive and statistically significant in Model (4), and consistent with Model (2), the coefficient for GOV×YEAR2008 in Model (4) is negative and statistically significant at the 1 percent level. The fiscal year dummies suggest that bank valuations were, on average, significantly lower in 2007 and especially in 2008. Inconsistent with our hypothesis, the estimates of Models (2) and (4) indicate that the depressed market valuation in 2008 amidst the market meltdown is largely attributable to banks with stronger corporate governance structures. However, it should be noted that this finding is broadly consistent with Beltratti and Stulz (2010), Erkens et al. (2010), and Fahlenbrach and Stulz (2011), who document that strong governance attributes are negatively associated with stock market performance during the crisis. Regarding the additional control variables, it can be noted that the market valuation of banks decreases with increasing amount of lending (LOANTA), increasing volatility (VOLA), and with negative earnings (LOSS). The adjusted R2s of about 51 percent and highly significant F-statistics again indicate a good fit of the estimated regression specifications. Overall, the results reported in Tables 3 and 4 demonstrate that corporate governance affects bank performance. Consistent with the prior literature, our findings indicate that strong governance generally improves financial performance and also has positive effects on market valuation. However, we find mixed evidence for our hypothesis that good corporate governance improved bank performance during the financial crisis. Although our findings suggest that banks with stronger corporate governance mechanisms were associated with significantly higher profitability during the financial crisis, our results also indicate that strong governance may have had negative effects on market valuations of banks amidst the crisis. Thus, inconsistent with the 13 research hypothesis, our results suggest that strong corporate governance does not necessarily create shareholder value in the banking industry during periods of severe market stress. Our empirical findings on the influence of corporate governance on bank performance are robust to several sensitivity tests. First, in order to ensure that the results are not affected by a few extreme observations, we winsorized the dependent variables (ROA and Q) as well as the control variables (SIZE, LEV, LOANTA, and VOLA) at the 1 percent and 99 percent levels and then re-estimated all regression models. The estimation results based on the winsorized data are consistent with those reported in Tables 3 and 4. Most importantly, the coefficients for the corporate governance variables are positive and statistically significant in the four regressions with ROA as the dependent variable, and positive and significant for GOV in Models (1), (2), and (4), and negative and significant for GOV×YEAR2008 in all the regressions with Q as the dependent variable. Furthermore, our results are robust to alternative variable definitions. We replaced GOV with a dummy variable that identifies the banks with Gov-Scores in the highest quartile (i.e., banks with the strongest corporate governance). Again, the estimation results are broadly consistent with our main findings. In the ROA regressions, the coefficients for GOV are positive and significant in Models (3) and (4), and the coefficient for GOV×YEAR2008 is positive and highly significant in Models (2) and (4). In the regressions with Tobin’s Q as the dependent variable, the estimated coefficients are positive and significant for GOV and negative and significant for GOV×YEAR2008 in all four model specifications. We also replaced ROA and Q with alternative variables. Our main results hold if return on assets is calculated as the ratio of net income to total assets and if Tobin’s Q is computed as the book value of assets plus the market value of equity less the book value of equity divided by the book value of total assets. 14 Thus, we conclude that our empirical findings are not sensitive to alternative variable definitions. Overall, the sensitivity tests provide further evidence to suggest that the strength of corporate governance is positively associated with financial performance and negatively associated with Tobin’s Q amidst the financial crisis. 3.2. Stock returns The preceding analysis indicates that banks with stronger corporate governance mechanisms had lower stock market valuations during the meltdown of financial markets in 2008. As the next step of the analysis, we examine the effects of corporate governance on bank stock returns around the financial crisis. First, we divide the banks into two subsamples based on the strength of corporate governance, and then calculate the mean and median stock returns in these subsamples for three distinct periods around the crisis. The banks with above median Gov-Scores comprise the stronger governance subsample and the weaker governance subsample consists of banks with below median Gov-Scores. The first period of analysis is from March 2007 to February 2008 and represents the onset of the crisis. The second period spans from March 2008 to February 2009, and thereby covers the period of the severe market stress. Finally, the third period extends from March 2009 through December 2009, and thus represents the stock market developments in the immediate aftermath of the crisis. (insert Table 5 about here) 15 The mean and median bank stock returns in different phases of the financial crisis are reported in Table 6. Interestingly, the table shows that banks with stronger corporate governance mechanisms slightly underperformed relative to banks with weaker governance at the onset and during the crisis. The documented more negative stock returns for banks with stronger governance are consistent with the Tobin’s Q regressions reported in Table 4, and also broadly consistent with the empirical findings reported in Beltratti and Stulz (2010), Erkens et al. (2010), and Fahlenbrach and Stulz (2011). However, both the t-tests and the Wilcoxon rank-sum tests indicate that the observed differences in stock returns between the stronger and weaker governance subsamples are not statistically significant. Contrary to the research hypothesis, our findings suggest that good corporate governance did not improve the stock market performance of banks during the financial crisis. Nevertheless, as can be noted from Table 6, banks with stronger corporate governance mechanisms provided substantially higher stock returns in the aftermath of the market meltdown from March 2009 onwards. The mean (median) stock return for the banks in the stronger governance subsample was about 86 percent (63 percent) during the ten month period from March 2009 to December 2009, while the corresponding mean (median) return for the banks in the weaker governance subsample was about 11 percent (13 percent). The t-tests and the Wilcoxon rank-sum tests indicate that the differences in stock returns between the two subsamples during the third period are statistically highly significant. Hence, our findings suggest that better corporate governance may have mitigated the adverse effects of the financial crisis on bank credibility among stock market participants. (insert Table 6 about here) 16 To further examine the association between corporate governance and bank stock returns, we estimate the following cross-sectional regression specification separately for the three periods around the financial crisis: rj 1 GOV j 2 BETA j 3 SIZE j 4 MB j j (2) where rj denotes stock return for bank j, GOV is the Gov-Score of Brown and Caylor (2006, 2009), BETA is the beta coefficient estimated against the S&P 500 index using 36 monthly return observations, SIZE is the logarithm of total assets, and MB is the market-to-book ratio calculated as the ratio of market value of equity to book value of equity. An extensive literature has documented that our control variables BETA, SIZE, and MB can explain a vast proportion of cross-sectional variation in stock returns. The estimates of Equation (2) are reported in Table 7. Consistent with Table 6 and inconsistent with our research hypothesis, the regression results indicate that the strength of corporate governance mechanisms is not statistically significantly related to bank stock returns during the first two analysis periods (03/2007 02/2008 and 03/2008 02/2009). However, the coefficient estimate for GOV is positive and significant at the 5 percent level in the third period (03/2009 12/2009). Hence, consistent with Table 6, our regressions indicate that the stock prices of the banks with stronger corporate governance structures recovered more quickly from the financial turmoil. The adjusted R2s of the stock return regressions vary between 29 and 49 percent. Regarding the control variables, it can be noted from Table 7 that the estimated coefficients for MB are positive and significant in all three regression specifications, while the coefficients for BETA and SIZE exhibit considerable variation across the turbulent periods. 17 Interestingly, the coefficient estimate for BETA is negative in the first period, thereby indicating that higher levels of systematic risk decreased bank stock returns at the onset of the financial crisis. Moreover, it should be noted that the coefficient for SIZE is negative and highly significant, suggesting that the largest banks had the lowest stock returns amidst the crisis. The regression results reported in Table 7 hold in two robustness checks. First, we estimated truncated versions of Equation (2) with GOV and BETA as the only independent variables. The estimates of these regressions are similar to Table 7; although being insignificant in the first two periods, the estimated coefficient for GOV is positive and highly significant in the third period that presents the immediate aftermath of the crisis. Second, we winsorized the stock returns as well as the control variables (BETA, SIZE, and MB) at the 1 percent and 99 percent levels in order to ensure that our results are not affected by outliers. Again, the coefficients for GOV are insignificant in the first two periods, while the coefficient estimate in the third period is positive and statistically significant. 4. CONCLUSIONS In this paper, we examine the association between corporate governance and bank performance during the financial crisis of 2008. Using data on large publicly traded U.S. banks, we examine the effects of corporate governance on profitability, market valuation, and stock returns amidst the crisis. In our empirical analysis, we apply the corporate governance index of Brown and Caylor (2006, 2009) to measure the strength of governance with banks. Given the extensive prior literature on the positive influence of good corporate governance on firm performance (see e.g., Ammann et al. 2011; Brown and Caylor 2006, 2009; Caprio et al. 2007; 18 Core et al. 2006; Gompers et al. 2003; Johnson et al. 2009; Sierra et al. 2006; Renders et al 2010), we hypothesize that banks with stronger governance mechanisms are associated with better financial and stock market performance during the crisis. Our empirical findings on the effects of corporate governance on bank performance during the financial crisis are mixed. Consistent with the research hypothesis, we find that banks with stronger corporate governance mechanisms had higher profitability in 2008, suggesting that good governance may have moderated the adverse influence of the financial crisis on financial performance. Nevertheless, our results also indicate that strong corporate governance practices may have had negative effects on stock market valuations of banks during the crisis, as banks with stronger governance are associated with lower Tobin’s Qs and stock returns amidst the crisis. Thus, inconsistent with the hypothesis, our findings suggest that good corporate governance did not create shareholder value in the banking industry during the market meltdown. However, we also document that banks with stronger corporate governance mechanisms provided substantially higher stock returns in the immediate aftermath of the market turmoil from March 2009 onwards. 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The descriptive statistics are reported separately (i) for the complete sample of 248 firm-year observations, (ii) for the financial crisis year 2008, (iii) for banks with stronger corporate governance, and (iv) for banks with weaker corporate governance. The stronger governance subsample consists of banks with above median Gov-Scores and the weaker governance subsample consists of banks with below median Gov-Scores. The reported pvalues are for two-tailed t-tests and Wilcoxon rank-sum tests of the null hypothesis that there is no difference between the stronger and weaker governance subsamples GOV Stronger governance Weaker governance ROA 2008 Stronger governance Weaker governance p-value Q 2008 Stronger governance Weaker governance p-value SIZE 2008 Stronger governance Weaker governance p-value LEV 2008 Stronger governance Weaker governance p-value Mean 31.435 35.387 27.484 1.913 0.313 2.114 1.712 (0.049) 1.061 0.996 1.058 1.064 (0.505) 9.989 10.117 10.940 9.038 (0.000) 0.899 0.897 0.900 0.898 (0.581) Median 32.500 35.000 28.000 2.210 1.179 2.392 2.049 (0.017) 1.058 0.978 1.063 1.052 (0.811) 9.495 9.521 10.914 8.905 (0.000) 0.902 0.897 0.903 0.901 (0.468) St. Dev. 4.469 1.779 2.336 1.608 2.251 1.439 1.743 Min 24.000 33.000 24.000 -6.083 -6.083 -4.967 -6.083 Max 40.000 40.000 32.000 5.108 4.508 5.108 4.073 0.074 0.066 0.072 0.075 0.905 0.905 0.915 0.905 1.275 1.268 1.193 1.275 1.625 1.667 1.618 0.930 7.147 7.731 8.437 7.147 14.598 14.477 14.598 11.893 0.031 0.031 0.029 0.034 0.727 0.809 0.813 0.727 0.977 0.977 0.948 0.977 24 Table 1 Continued. LOANTA 2008 Stronger governance Weaker governance p-value VOLA 2008 Stronger governance Weaker governance p-value LOSS 2008 Stronger governance Weaker governance p-value Mean 66.348 67.588 62.550 70.146 (0.000) 28.198 57.239 26.368 30.028 (0.235) 0.121 0.403 0.121 0.121 (1.000) Median 69.000 70.025 67.121 71.268 (0.000) 19.469 48.929 16.308 22.977 (0.013) 0.000 0.000 0.000 0.000 (1.000) St. Dev. 12.637 12.558 14.831 8.465 Min 16.541 18.291 16.541 50.492 Max 93.650 85.799 82.298 93.650 24.246 31.551 24.040 24.410 6.884 17.979 6.929 6.884 170.558 170.558 170.558 152.341 0.327 0.495 0.327 0.327 0.000 0.000 0.000 0.000 1.000 1.000 1.000 1.000 25 Table 2 Correlations. The table reports pairwise correlations for the variables used in the empirical analysis: (i) The dependent variables are bank performance measures ROA (return on assets) and Q (Tobin’s Q). (ii) The strength of corporate governance is measured by GovScore (GOV). (iii) Firm-specific control variables are defined as follows: SIZE is the logarithm of total assets, LEV is financial leverage measured as the ratio of total liabilities to total assets, LOANTA is loans to total assets, VOLA is the annualized volatility of stock returns, and LOSS is a dummy variable that equals one for banks that report negative earnings during the fiscal year ROA 0.067 Q -0.049 0.585 *** SIZE 0.592 *** -0.069 -0.236 *** LEV 0.101 -0.132 ** 0.129 ** 0.124 * GOV ROA Q SIZE LEV LOANTA VOLA ***, **, and * denote significance at the 0.01, 0.05, and 0.10 levels, respectively LOANTA -0.295 *** -0.163 ** -0.121 * -0.279 *** -0.188 *** VOLA -0.129 ** -0.619 *** -0.561 *** -0.041 0.089 0.061 LOSS 0.041 -0.767 *** -0.517 *** 0.120 * 0.118 * 0.123 * 0.611 *** 26 Table 3 Corporate governance and profitability. The table reports the estimates of the following panel regression specification: ROA j ,t 1 GOV j ,t 2 GOV j ,t YEAR 2008 j 3 SIZE j ,t 4 LEV j ,t 2008 5 LOANTA j ,t 6 VOLA j ,t 7 LOSS j ,t y YEAR jy j ,t y 2006 where ROAj,t denotes return on assets for bank j at time t, GOVj,t is the Gov-Score of Brown and Caylor (2006, 2009), SIZEj,t is the logarithm of total assets, LEVj,t is financial leverage measured as the ratio of total liabilities to total assets, LOANTAj,t is loans to total assets, VOLAj,t is the logarithm of annualized volatility of stock returns, LOSSj,t is a dummy variable that equals one for banks that report negative earnings during year t, and YEARjy is a dummy variable for years. The t-statistics (reported in parenthesis) are based on standard errors corrected for clustering at the bank level Variable Constant GOV Model (1) 9.413 *** (2.67) 0.052 ** (2.30) GOV × YEAR2008 Model (2) 9.469 *** (2.64) 0.049 ** (2.35) Model (3) 6.892 *** (3.53) 0.039 *** (2.63) Model (4) 7.039 *** (3.33) 0.030 *** (3.42) -0.062 (-1.36) -4.396 ** (-2.02) -0.009 ** (-2.22) -0.126 (-1.46) -2.911 *** (-6.79) 0.035 *** (5.04) -0.062 (-1.36) -4.157 ** (-2.01) -0.009 ** (-2.20) -0.153 (-1.51) -2.908 *** (-6.80) -0.104 (-1.28) -8.223 ** (-2.16) 0.014 ** (2.20) -0.104 (-1.28) -8.159 ** (-2.15) YEAR2006 -0.077 *** (-7.76) -0.077 *** (-7.78) -0.064 *** (-5.89) -0.066 *** (-5.52) YEAR2007 -0.456 *** (-113.31) -0.456 *** (-110.41) -0.162 *** (-4.38) -0.156 *** (-3.78) YEAR2008 -2.319 *** (-665.58) -2.768 *** (-13.73) -0.962 *** (-5.90) -2.047 *** (-9.09) Adjusted R2 0.367 0.365 0.649 F-stat. 24.899 *** 21.280 *** 51.697 *** ***, **, and * denote significance at the 0.01, 0.05, and 0.10 levels, respectively 0.649 46.700 *** SIZE LEV LOANTA VOLA LOSS 27 Table 4 Corporate governance and market valuation. The table reports the estimates of the following panel regression specification: Q j ,t 1 GOV j ,t 2 GOV j ,t YEAR 2008 j 3 SIZE j ,t 4 LEV j ,t 2008 5 LOANTA j ,t 6 VOLA j ,t 7 LOSS j ,t y YEAR jy j ,t y 2006 where Qj,t denotes Tobin’s Q for bank j at time t, GOVj,t is the Gov-Score of Brown and Caylor (2006, 2009), SIZEj,t is the logarithm of total assets, LEVj,t is financial leverage measured as the ratio of total liabilities to total assets, LOANTAj,t is loans to total assets, VOLAj,t is the logarithm of annualized volatility of stock returns, LOSSj,t is a dummy variable that equals one for banks that report negative earnings during year t, and YEARjy is a dummy variable for years. The coefficients for GOV and GOV×YEAR2008 are multiplied by 100 in order to facilitate interpretation. The t-statistics (reported in parenthesis) are based on standard errors corrected for clustering at the bank level Variable Constant GOV Model (1) 0.900 *** (26.83) 0.173 *** (4.91) Model (2) 0.888 *** (20.41) 0.252 *** (6.82) -0.013 *** (-6.67) 0.304 *** (5.05) -0.314 *** (-43.31) -0.013 *** (-6.71) 0.290 *** (5.45) GOV × YEAR2008 SIZE LEV LOANTA VOLA LOSS Model (3) 0.929 *** (17.32) 0.079 (1.02) Model (4) 0.921 *** (15.33) 0.132 ** (2.05) -0.013 *** (-11.08) 0.432 *** (3.81) -0.000 * (-1.89) -0.031 * (-1.79) -0.051 *** (-4.26) -0.203 *** (-3.30) -0.013 *** (-11.12) 0.419 *** (3.84) -0.000 * (-1.94) -0.029 * (-1.74) -0.051 *** (-4.48) YEAR2006 0.000 (0.66) 0.000 (0.55) YEAR2007 -0.056 *** (-111.52) -0.056 *** (-117.93) -0.043 *** (-10.10) -0.044 *** (-10.29) YEAR2008 -0.102 *** (-127.36) -0.004 * (-1.94) -0.044 *** (-2.64) 0.018 ** (2.27) -0.002 (-1.50) Adjusted R2 0.415 0.420 0.509 F-stat. 30.232 *** 26.523 *** 29.490 *** ***, **, and * denote significance at the 0.01, 0.05, and 0.10 levels, respectively -0.002 (-1.42) 0.510 26.721 *** 28 Table 5 Corporate governance and stock returns. The table reports the mean and median bank stock returns for three periods: (i) March 2007 to February 2008, (ii) March 2008 to February 2009, and (iii) March 2009 to December 2009. The stronger governance subsample consists of banks with above median Gov-Scores and the weaker governance subsample consists of banks with below median Gov-Scores. The reported p-values are for two-tailed ttests and Wilcoxon rank-sum tests of the null hypothesis that there is no difference in stock returns between the stronger and weaker governance subsamples All banks Stronger governance Weaker governance Difference p-value 03/2007 – 02/2008 Mean Median -30.07 -29.37 -31.53 -31.55 -28.61 -26.37 -2.92 -5.18 (0.590) (0.559) 03/2008 – 02/2009 Mean Median -55.40 -57.24 -56.79 -58.60 -54.01 -53.98 -2.78 -4.63 (0.694) (0.569) 03/2009 – 12/2009 Mean Median 46.47 36.91 85.73 63.21 11.01 12.86 74.72 50.36 (0.001) (0.000) 29 Table 6 Corporate governance and stock returns. The table reports the estimates of the following cross-sectional regression specification: rj j 1 GOV j 2 BETA j 3 SIZE j 4 MB j where rj denotes stock return for bank j, GOVj is the Gov-Score of Brown and Caylor (2006, 2009), BETAj is the beta coefficient calculated against the S&P 500 index, SIZEj is the logarithm of total assets, and MBj is the market-to-book ratio calculated as the ratio of market value of equity to book value of equity. The t-statistics (reported in parenthesis) are based on White’s heteroskedasticity consistent standard errors Variable Constant GOV BETA SIZE MB 03/2007 – 02/2008 -0.200 (-0.96) -0.007 (-1.32) -0.084 ** (-2.37) -0.002 (-0.15) 0.143 *** (5.59) 03/2008 – 02/2009 -0.457 ** (-2.34) 0.012 (1.61) -0.057 (-1.63) -0.063 *** (-3.24) 0.179 *** (4.60) Adjusted R2 0.294 0.487 F-stat. 7.341 *** 15.506 *** ***, **, and * denote significance at the 0.01, 0.05, and 0.10 levels, respectively 03/2009 – 12/2009 -2.451 *** (-3.43) 0.045 ** (2.01) 0.754 *** (3.02) 0.037 (0.51) 0.305 *** (3.10) 0.464 12.897 *** 30 Appendix 1 List of banks. 1 2 3 4 5 6 7 8 9 10 11 12 13 14 15 16 17 18 19 20 21 22 23 24 25 26 27 28 29 30 31 32 33 34 35 36 37 38 39 40 View publication stats Associated Banc-Corp. Astoria Financial Corp. Bank Mutual Corp. Bank Of America Corp. Bank Of Hawaii Corp. Bank Of New York Mellon Corp. Boston Private Financial Holdings Inc Brookline Bancorp Inc Capital One Financial Corp. Cascade Bancorp Citigroup Inc City National Corp. Comerica Inc Community Bank System Inc Cullen Frost Bankers Inc Dime Community Bancshares Inc East West Bancorp Inc Fifth Third Bancorp First Commonwealth Financial Corp. First Financial Bancorp First Horizon National Corp. First Midwest Bancorp Inc First Niagara Financial Group Inc Firstmerit Corp. Flagstar Bancorp Inc Glacier Bancorp Inc Huntington Bancshares Inc Irwin Financial Corp. Keycorp M & T Bank Corp. Marshall & Ilsley Corp. New York Community Bancorp Inc Northern Trust Corp. PNC Financial Services Group Inc Privatebancorp Inc Provident Bankshares Corp. Regions Financial Corp. South Financial Group Inc Sovereign Bancorp Inc Sterling Bancshares Inc 41 42 43 44 45 46 47 48 49 50 51 52 53 54 55 56 57 58 59 60 61 62 Sterling Financial Corp. Suntrust Banks Inc Susquehanna Bancshares Inc SVB Financial Group SWS Group Inc Synovus Financial Corp. TCF Financial Corp. Trustco Bank Corp. NY Ucbh Holdings Inc Umpqua Holdings Corp. United Bankshares Inc US Bancorp Wachovia Corp. Washington Federal Inc Washington Mutual Inc Webster Financial Corp. Wells Fargo & Co Westamerica Bancorporation Whitney Holding Corp. Wilmington Trust Corp. Wintrust Financial Corp. Zions Bancorporation