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Erschienen in: Journal of Business Ethics 2/2015

13.08.2014

Religiosity and Earnings Management: International Evidence from the Banking Industry

verfasst von: Kiridaran Kanagaretnam, Gerald J. Lobo, Chong Wang

Erschienen in: Journal of Business Ethics | Ausgabe 2/2015

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Abstract

Using an international sample of banks, we study how differences in religiosity across countries affect earnings management. Given that religiosity is a major source of morality and ethical behavior, it may reduce excessive risk taking and act as deterrence for earnings manipulations. Therefore, we predict lower earnings management in societies that have higher religiosity. Consistent with expectations, our cross-country analysis indicates that religiosity is negatively related to income-increasing earnings management for loss-avoidance and just-meeting-or-beating prior year’s earnings. We also find that religiosity reduces income-increasing earnings management through abnormal loan loss provisions. In additional tests, we document that religiosity increases the information value of bank earnings, with both earnings persistence and cash flow predictability being enhanced by higher religiosity. For the crisis period analysis (i.e., 2007–2009), our evidence shows that banks in countries with higher religiosity exhibit lower probability of reporting asset deterioration and lower probability of having poor performance.

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Fußnoten
1
Prior research documents that religion affects, among other things, individuals’ wages (Chswick 1983), level of education (Chswick 1985; Gruber 2005), criminal behavior (Evans et al. 1995), risk aversion (Miller and Hoffman 1995; Halek and Eisenhauer 2001), and social ethics (Arruñada 2010).
 
2
Prior research argues that proxies of abnormal accruals commonly used to detect earnings management are subject to serious measurement error (Guay et al. 1996; McNichols 2000, 2002; Jones et al. 2008). For example, McNichols (2002) questions the construct validity of a proxy based on aggregate accruals because of the complexity associated with modeling the estimation errors in aggregate accruals.
 
3
We obtain similar inferences for all our main tests, when we replace the aggregate religiosity variable with the three individual dimensions of religion.
 
4
It is generally accepted that the most recent financial crisis in the US and UK started in 2007 (Ryan 2008). However, the financial crisis spread to other countries in 2008 (Laeven and Valencia 2010).
 
5
A survey of managers by Graham et al. (2005) finds that just-meeting-or-beating prior period’s earnings is one of the most important benchmarks for corporate managers. In addition, Burgstahler and Dichev (1997) and Degeorge et al. (1999) provide empirical evidence indicating that loss-avoidance is also an important benchmark for managers.
 
6
Since bank size is highly correlated with all four of our religion variables, we include size in separate regressions with other country level variables.
 
7
These variables have also been used in several prior studies (e.g., Wahlen 1994; Kanagaretnam et al. 2004) to estimate the normal component of LLP.
 
8
The 29 countries in our sample are all represented in the three most recent World Values Surveys. We match bank-year financial data with the most recent survey to obtain the religious values.
 
9
We extend the sample period to 2009 to compute large loan loss provisions and poor performance during the crisis period.
 
10
We follow Alam (2001) to set 500 millions of total assets as big banks criterion.
 
11
We winsorize each of the continuous control variables used in Eqs. (1)–(3) at the top and bottom one percent to remove the effects of extreme values.
 
12
The marginal effect per standard deviation (SD) change for a religious variable is computed as p × (1 − p) × β × SD, where p is the base rate (0.11) and β is the estimated coefficient from the logistic regression (Liao 1994).
 
13
The impact of a one standard deviation increase in religion (RELIGIOSITY) on income-increasing abnormal LLP is computed as −0.002 (coefficient on RELIGIOSITY) × 0.244 (the sample standard deviation of RELIGIOSITY) ÷ 0.002 (the mean of Income-increasing ALLP) = −24.4 %. The other comparative statics are computed analogously.
 
14
In addition to these sensitivity checks, we also examine whether our results are robust to country-year clustering. Overall, we find that our results still hold after clustering by country-year instead of by firm-year.
 
15
Prior research in banking (e.g., Wahlen 1994) uses earnings before taxes and loan loss provisions as a proxy for cash flow, since loan loss provisions are the single largest accrual for banks.
 
16
We terminate our sample period in 2005 to avoid the abnormal crisis period fluctuations in earnings and cash flows.
 
17
As a sensitivity test, we re-estimate model (6) after pooling the crisis and non-crisis periods together, and adding a crisis period indicator variable and its interaction with Religiosity to the model. We find that the coefficient on the interaction term is insignificant for the LARGE_LLP regression but is negative and significant for the POOR_PERFORMANCE regression, indicating that the effects of religiosity on POOR_PERFORMANCE are more pronounced during the crisis period.
 
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Metadaten
Titel
Religiosity and Earnings Management: International Evidence from the Banking Industry
verfasst von
Kiridaran Kanagaretnam
Gerald J. Lobo
Chong Wang
Publikationsdatum
13.08.2014
Verlag
Springer Netherlands
Erschienen in
Journal of Business Ethics / Ausgabe 2/2015
Print ISSN: 0167-4544
Elektronische ISSN: 1573-0697
DOI
https://doi.org/10.1007/s10551-014-2310-9

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