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Erschienen in: Review of Quantitative Finance and Accounting 1/2013

01.01.2013 | Original Research

Asset write-offs discretion and accruals management in Taiwan: the role of corporate governance

verfasst von: Chia-Ling Chao, Shwu-Min Horng

Erschienen in: Review of Quantitative Finance and Accounting | Ausgabe 1/2013

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Abstract

Using a sample of Taiwan’s public firms, this paper examines whether managers use discretionary write-offs and abnormal accruals jointly to reach earnings targets and how corporate governance mechanisms react to such opportunistic behavior. We develop a set of simultaneous equations that capture executives’ incentives to manage earnings through write-offs and accrual management. These incentives include the existence and tightness of accounting-based covenants, “big bath,” income smoothing, and changes in senior management. The empirical results show that firms with larger discretionary write-offs also have lower discretionary accruals. In addition, we find that these earnings management tools are endogenous, suggesting that discretionary write-offs and discretionary accruals are partial complements for earnings manipulation and that their magnitudes are determined jointly. These findings contrast sharply with the tenor of discussion in the U.S. literature concerning the potential for using asset write-offs and discretionary accruals to manipulate earnings, which documents that managers use their discretion over accruals to signal economic realities rather than to obfuscate. Moreover, the results reveal that the empirical association between discretionary write-offs and abnormal accruals is more pronounced in weakly governed firms, suggesting that a strong governance setting is likely to constrain management’s discretionary behavior. The above implications are robust to a number of alternative specifications and variables definitions.

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Fußnoten
1
The FASC does not allow increases in goodwill values and subsequent reversals of previously recognized impairment losses for goodwill. However, for long-lived assets other than goodwill, the impairment losses can be reversed if market conditions have improved, but only to the extent that the book value of the asset after the reversal may not exceed the asset’s book value before the impairment loss was recognized, less a required provision for depreciation or amortization. As of December 31, 2007, few companies (less than 6% of public firms) have recognized the restoration of previously recognized impairment losses.
 
2
Although the measurement of discretionary accruals plays a central role in a wide body of accounting literature, Rees et al. (1996) is one of the few studies to examine accounting policy choices jointly (i.e., abnormal accruals in the year of the asset write-off) in the context of the accrual management literature. Following Rees et al., Yen and Chao (2009) investigate the association between the entire amount of asset impairment losses and discretionary accruals. However, both studies do not test for the existence of endogeneity. Examples of other studies are Barton (2001) and Huang et al. (2009), who document that managers use financial derivatives and discretionary accruals as partial substitutes for earnings management.
 
3
The big bath hypothesis suggests that in periods when performance is poor, management may take the opportunity to report other discretionary bad news. That is, if a manager cannot manipulate earnings to reach a “target” level, he/she will attempt to decrease current earnings in favor of increasing future earnings and, therefore, future bonuses.
 
4
The income smoothing hypothesis posits that firms may manage earnings to reduce fluctuations around some level considered normal for the firm. Specifically, when earnings are unusually high, firms are likely to choose income-reducing accruals; when earnings are unusually low, they are likely to take income-increasing accruals.
 
5
IFRS include standards issued by the current standard-setting body (the IASB) and the standards issued by its predecessor (the International Accounting Standards Committee, IASC), some of which the IASB has amended. More than 100 countries now require or permit the use of IFRS, or are converging with the IASB’s standards.
 
6
Several methods have been proposed in the literature for separating operating accruals into normal (nondiscretionary) and abnormal (discretionary) components (see later sections and Kothari et al. 2005, for a review of these models). In these models, parameters are estimated for normal accrual activity by regressing an accounting accrual measure on proxies for normal business activity. These estimated normal accrual parameters and the event-period data are then combined to generate unexpected accrual activity.
 
7
An ideal economic factor would include managers’ expectations of the asset(s)’ future performance, as this is vital to evaluating asset impairment. Given that these expectations are generally unobservable, we follow prior research (in particular, Francis et al. 1996; Riedl 2004) and choose alternative proxies likely to reflect managers’ expectations to some extent.
 
8
Following Godfrey and Koh (2009), we include LOSS it as an additional explanatory variable in the write-off decision analysis.
 
9
We use the cross-sectional approach, rather than the time-series approach, to measure discretionary accruals. The cross-sectional approach has an advantage in that it controls for the effects of changing industry-wide economic conditions (Teoh et al. 1998a, b). Further, prior research (e.g., Bartov et al. 2001) documents that the cross-sectional approach outperforms its time-series counterpart in detecting earnings management. The assumption underlying the former is that firms in the same industry have a similar operating cycle; the latter assumes that the length of a firm’s operating cycle does not change over the estimation and event period (Bartov et al. 2001). The results (not reported) show that our sample firms are not much different from the average firm in their respective industry. Thus, the fact that our model coefficients estimated from cross-sectional regressions are the same for all firms in the industry should not represent a serious problem.
 
10
Prior studies (e.g., Altman 1968; Ohlson 1980; Shumway 2001; Zmijewski 1984) have developed several models using somewhat overlapping sets of financial ratios to estimate a firm’s risk of bankruptcy. Although these statistical models have been widely used in bankruptcy prediction, option pricing models (e.g., the approach developed by Black and Scholes 1973 and Merton 1974) have gained in popularity. As various studies (e.g., Gharghori et al. 2006; Hillegeist et al. 2004; Patel and Pereira 2007; Vassalou and Xing 2004) document, the option pricing bankruptcy risk measures outperform those based on traditional statistical models.
 
11
Mensah (1984) indicates that users of bankruptcy prediction models need to recognize that such models may require redevelopment from time to time to take into account changes in the economic environment that may affect the financial condition of firms examined. Most academic research on predicting financial distress has been conducted on U.S. firms. However, extant research documents that Altman’s Z-score remains valid in principle for predicting the bankruptcy of Japanese companies (e.g., Xu and Zhang 2009) and Chinese companies (e.g., Wang and Campbell 2010). Given that Taiwan may share some economic growth patterns with Japan and China due to geographic location, cultural resemblance, and similar economic-development strategies (Holz 2005), we adopt Altman’s model to determine the bankruptcy risk for our sample firms.
 
12
Altman’s (1968) model is the most well known and often used in practice for predicting financial distress (in particular, bankruptcy). Specifically, Altman’s Z-score = 1.2 × Working Capital/Total Assets + 1.4 × Retained Earnings/Total Assets + 3.3 × Earnings before Interest and Taxes/Total Assets + 0.6 × Market Value of Equity/Book Value of Total Liabilities + 0.999 × Sales/Total Assets. A firm with a higher Z-score is considered to have a lower probability of corporate failure.
 
13
A proxy for management compensation could also be included in the analysis. However, prior research (e.g., Healy 1985) indicates that the details of the bonus calculations vary across plans. Managers’ incentives to report higher earnings in a given year may vary with these details. Because it is difficult to get enough details about compensation arrangements, more general proxies for BBATH it and SMOOTH it are used in the analyses.
 
14
SMOOTH it is the proxy for “income smoothing” reporting, which is set equal to SM_ROA it or SM_DIS it . Specifically, SM_ROA it is equal to the difference between firm i’s earnings (measured before discretionary write-offs and DCA_ROA it ) for year t and earnings for year t − 1, divided by total assets at the end of t − 1, when this change is either above the median of nonzero positive values or below the median of nonzero negative values of this variable, and 0 otherwise; SM_DIS it is equal to the difference between firm i’s earnings (measured before discretionary write-offs and DCA_DIS it ) for year t and earnings for year t − 1, divided by total assets at the end of t − 1, when this change is either above the median of nonzero positive values or below the median of nonzero negative values of this variable, and 0 otherwise.
 
15
All of our sample firms have elected supervisors, but only 1% of the sample observations have set up audit committees. Therefore, we do not include audit committees as a governance factor.
 
16
The unit-weighting approach is widely used in the corporate governance literature. Some researchers refer to the sum of raw item values across components as unit weights, while others use the term to refer to summing standardized values (Bobko et al. 2007). We adopt this latter definition (i.e., the values for each governance attribute are converted into z-scores before applying equal weights) because the variance of the raw item values can have a substantial influence on the effective weight of an individual governance variable in the composite measure.
 
17
An alternative would be to use principal component analysis (PCA) to construct the summary governance measure. PCA automatically generates weights so that the composite measure will explain much of the variance in the group of corporate governance characteristics and, therefore, does not require the ex ante determination of the weights (Florackis and Ozkan 2009). However, compared to factor analytic procedures, the unit-weighting approach of constructing variables has been proved to exhibit less variance and greater generalizability (i.e., values are less sample-specific) (Emerson et al. 2009). In addition, prior research demonstrates that average z-scores correlate highly with different weighting schemes, such as factor analysis, and that using the average z-score is considered a better approach than summing the raw item values for a total score in the presence of missing data (see McKnight et al. 2007). Accordingly, we use unit weights to construct GOV it following the recommendations of Grice and Harris (1998), who document that the unit-weighting approach exhibits high consistency across independent samples and retains many of the desirable attributes of regression-based factor scores while being less subject to the problems associated with using the same data to estimate the coefficients.
 
18
Business Groups in Taiwan, published annually by the China Credit Information Service, provides demographic information on the top 100 business groups in Taiwan in terms of asset, sales, employees, group age, background of top management teams, and inter-company relationship within a group.
 
19
In contrast with prior U.S.-based research on asset impairment, Taiwan’s relevant studies (e.g., Chao 2007; Young and Wu 2009) find that write-off firms are more highly leveraged than non-write-off firms.
 
20
Untabulated results show that the Heckman first-stage probit estimation in Eq. 2 used to compute MILL it has a pseudo R 2 of 21%, and that MB it (p-value < 0.01), ∆ROA it (p-value < 0.05), LOSS it (p-value < 0.01), and SIZE it (p-value < 0.01) appear to explain significantly the decision to write-down assets. Specifically, the coefficients of the independent variables in the probit estimation are qualitatively similar to the second-stage tests in Eq. 3 as reported in column 3 of Table 5. We also examined several variations of the first-stage probit model, altering several independent variables. In general, the results reported in this paper for the first-stage estimation and the second-stage tests are robust to alternative specifications.
 
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Metadaten
Titel
Asset write-offs discretion and accruals management in Taiwan: the role of corporate governance
verfasst von
Chia-Ling Chao
Shwu-Min Horng
Publikationsdatum
01.01.2013
Verlag
Springer US
Erschienen in
Review of Quantitative Finance and Accounting / Ausgabe 1/2013
Print ISSN: 0924-865X
Elektronische ISSN: 1573-7179
DOI
https://doi.org/10.1007/s11156-011-0269-5

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