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What Do We Know about Variance in Accounting Profitability? Author(s): Anita M. McGahan and Michael E. Porter Source: Management Science, Vol. 48, No. 7 (Jul., 2002), pp. 834-851 Published by: INFORMS Stable URL: http://www.jstor.org/stable/822694 Accessed: 20-02-2017 03:43 UTC JSTOR is a not-for-profit service that helps scholars, researchers, and students discover, use, and build upon a wide range of content in a trusted digital archive. We use information technology and tools to increase productivity and facilitate new forms of scholarship. For more information about JSTOR, please contact support@jstor.org. Your use of the JSTOR archive indicates your acceptance of the Terms & Conditions of Use, available at http://about.jstor.org/terms INFORMS is collaborating with JSTOR to digitize, preserve and extend access to Management Science This content downloaded from 146.155.94.33 on Mon, 20 Feb 2017 03:43:41 UTC All use subject to http://about.jstor.org/terms What Do We Know About Variance in Accounting Profitability? Anita M. McGahan * Michael E. Porter Boston University School of Management, 595 Commonwealth Avenue, Boston, Massachusetts 02215 Harvard Business School, Soldiers Field, Boston, Massachusetts 02163 amcgahan@bu.edu * mporter@hbs.edu In this paper, we analyze the variance of accounting profitability among a broad cross- section of firms in the American economy from 1981 to 1994. The purpose of the analysis is to identify the importance of year, industry, corporate-parent, and business-specific effects on accounting profitability among operating businesses across sectors. The findings indicate that industry and corporate-parent effects are important and related to one another. As expected, business-specific effects, which arise from competitive positioning and other factors, have a large influence on performance. The analysis reconciles the results of previous studies by exploring differences in method and data. We also identify the broad contributions and limi- tations of the research, and suggest avenues for further study. New approaches are necessary to generate significant insights about the relationships between industry, corporate-parent, and business influences on firm profitability. (Performance; Sustainability; Industry Structure; Corporate Strategy) 1. Introduction Researchers in the economics and strategy fields have long been interested in understanding the determi- nants of firm profitability. During the 1960s and 1970s, a large empirical literature in industrial organiza- tion employed cross-sectional regression analysis to explain firm performance based on industry character- istics, including seller concentration, advertising, and R&D intensity. The aim was to explore the relationship between structural entry barriers, tacit collusion, and industry performance. These studies were challenged in the 1980s because they tended to assume that indus- try structure is fixed independently of firm perfor- mance. In a review of the literature, Schmalensee (1989) reinterpreted the structure-performance find- ings as descriptive of empirical regularities rather than as conclusive evidence of causal relationships. Viewed in this way, the literature of the 1960s and 1970s on firm performance generated important insights about the variation in accounting profitability. MANAGEMENT SCIENCE ? 2002 INFORMS Vol. 48, No. 7, July 2002 pp. 834-851 Partly in response to the limits of the early research, a new style of work emerged in the 1980s. This new approach, pioneered by Schmalensee (1985), decom- posed the variance in profitability across business seg- ments into components associated with year, industry, the corporate-parent, and business-specific effects.1 Over the past dozen years, several studies in this research stream have explored profit variance (Rumelt 1991, Roquebert et al. 1996, McGahan and Porter 1 During the mid-1980s, questions were raised about the informa- tion contained in accounting returns about real economic activ- ity. The classic expression of concern by Fisher and McGowan (1983) emphasized that accounting returns do not capture the net present value of all returns on investment. A famous debate, which included comments by Horowitz (1984), Long and Ravenscraft (1984), Martin (1984), Van Breda (1984), and a reply by Fisher (1984), raised questions about whether or not accounting rates of return reflect monopoly rents and whether or not booked assets are fairly depreciated. In this study, we investigate the importance of year, industry, business-specific, and corporate-parent effects on account- ing profitability, but do not address the sources of the effects. 0025-1909/02/4807/0834$5.00 1526-5501 electronic ISSN This content downloaded from 146.155.94.33 on Mon, 20 Feb 2017 03:43:41 UTC All use subject to http://about.jstor.org/terms McGAHAN AND PORTER Variance in Accounting Profitability 1997a), yielding somewhat different conclusions. The purpose of these studies was to describe the impor- tance of industry, corporate-parent, and business influences on profitability. Despite the advances asso- ciated with the new approach, the generality of results has been limited by breadth of data and statistical limitations. This first objective of this study is to reconcile results from various studies in the recent literature on vari- ation in profitability. A second objective is to obtain new results based on a broad dataset and methods that are less restrictive than those used in the previous studies. The analysis relies on a dataset that includes all publicly traded firms in the American economy over an extended period. The methods employed in this study also drop certain restrictive assumptions about the underlying economic processes that had been incorporated in the methodologies of the earlier studies. 2. Studies on the Decomposition of Variance in Business-Specific Accounting Profitability The studies of variance in business-specific account- ing profitability were developed in response to limita- tions in the predecessor research on structural models. The structural models incorporated the assumption that industry structure shaped firm conduct, which in turn drove firm performance. This assumption implicitly ruled out alternative directions of causal- ity. No provisions were made for the possibility that conduct was driven by performance, or that conduct influenced industry structure. By the mid-1980s, a "new empirical industrial organization" gained favor over the classical "structure/conduct/performance" models (Bresnahan 1989). The new approach empha- sized detailed industry studies that could account for feedback between performance, conduct, and struc- ture.2 Separately, a small group of authors continued the large-scale statistical analyses, but with methodolo- gies that did not impute causal relationships between 2For example, principal-agent studies examined the influence of managerial conduct on performance simultaneously with the influ- ence of performance on managerial conduct. industry structure, business conduct, and firm per- formance (Schmalensee 1985, Rumelt 1991, Werner- felt and Montgomery 1988). These studies sought to document relationships without stipulating causal- ity. The advantage was the robustness of the find- ings. The variance-decomposition literature was an important complement to studies in the "new empiri- cal industrial organization" because it established the general importance of industry, corporate, and busi- ness effects on firm performance. A disadvantage of the approach was an inherent limitation in the power of the claims about the drivers of performance. Table 1 summarizes studies that decompose the variance of accounting profitability.3 The first col- umn of Table 1 reproduces Schmalensee's seminal results. Schmalensee (1985) used the 1975 FTC Line- of-BusinessSurvey to study the effects of indus- try on variance in business-unit accounting profit in manufacturing industries. Because his data cov- ered a single year, he could not identify either year or business-specific effects on variance in profitabil- ity. Instead, Schmalensee (1985) tested for evidence of business-specific differences through a single, exogenous measure of market share. His analy- sis also included corporate-parent effects, which he called "firm effects." Schmalensee found that industry effects accounted for about 20% of variance, market- share effects accounted for less than 1% of variance, and corporate-parent effects did not significantly con- tribute to variance. He concluded that managerial influences were not important compared to differ- ences in industry structure. The second major advance in recent research on the components of accounting profit was Rumelt (1991). By studying the business-unit accounting profit of the manufacturing firms covered in the FTC Survey for more than one year (i.e., for 1974-1977), Rumelt reported on the amount of variance that persisted over the entire period but that could not be attributed 3 The studies also generated interest in the decomposition of other measures of firm performance, including Tobin's q (Wernerfelt and Montgomery 1988, McGahan 1999a) and market share (Chang and Singh 2000). Mauri and Michaels (1997) supplement findings in the research stream by decomposing variance in advertising and R&D ratios across undiversified manufacturers. Only studies on account- ing profit are reviewed here. MANAGEMENT SCIENCE/Vol. 48, No. 7, July 2002 835 This content downloaded from 146.155.94.33 on Mon, 20 Feb 2017 03:43:41 UTC All use subject to http://about.jstor.org/terms McGAHAN AND PORTER Variance in Accounting Profitability Table 1 Results on the Decomposition of Variance in Business-Specific Accounting Profit (1) (2) (3) (4) (5) (6) Schmalenseea Rumeltb Rumeltc Roquebert et al.d McGahan & Portere McGahan & Porterf Method COVg COV Nested ANOVAh COV COV Nested ANOVA Source of data FTC FTC FTC Compustat Compustat Compustat Years covered 1975 1974-1977 1974-1977 1985-1991 1981-1994 1981-1994 Sectoral coverage Manuf. Manuf. Manuf. Manuf. All All No. of observations 1,775 6,931 6,931 16,596 58,132 58,132 Year N/A N/A 0.03 N/A 2.39 0.3 Industry 19.59 8.32 17.9 10.2 18.68 9.4 Corporate-parent N/A 0.80 14.8 17.9 4.33 9.1 Segment-specific N/A N/A N/A 37.1 31.71 35.1 Business-unit N/A 46.37 33.9 N/A N/A N/A Industry-market-share covariance -0.62 N/A N/A N/A N/A N/A Corporate-parent-industry covariance N/A N/A N/A N/A -5.51 N/A Market share 0.62 N/A N/A N/A N/A N/A Industry-year N/A 7.84 9.8 2.3 N/A N/A Model 19.59 63.33 76.5 68.0 51.60 66.8' Error 80.41 36.87 23.5 32.0 48.40 33.2 Total 100.00 100.00 100.0 100.00 100.00 100.00 Notes. aResults from Schmalensee (1985, Table 1, p. 348). bResults from Rumelt (1991, Dataset A as reported in Table 3, p. 178). CResults from Rumelt (1991, Dataset A as reported in Table 2, Panel (a), p. 177). dResults from Roquebert et al. (1996, as reported in Table 4, p. 661). eResults from McGahan and Porter (1997a, as reported in Table 2). 'Results from McGahan and Porter (1997a, as reported in Table 5, Panel (a)). gComponents-of-variance technique. hNested analysis-of-variance technique. 'Includes 12.9% of variance explained by a null model accounting for serial correlation in errors. to year, industry, or corporate-parent effects. This sta- ble portion of variance, attributable to "business-unit effects," captured the entire effect of competitive- positioning differences, and was more general than the market-share measure used by Schmalensee (1985). (Rumelt's (1991) fixed business-unit effects captured not only competitive-positioning effects but also any other persistent source of idiosyncratic dif- ferences.) A central purpose of Rumelt's (1991) paper was to refute Schmalensee's (1985) suggestion about management by showing that business-unit effects were more important than industry effects. Columns (2) and (3) of Table 1 show the results of Rumelt's (1991) analyses. Using both components- of-variance and ANOVA techniques, Rumelt found that business-unit effects accounted for substantially more of variance than either industry or corporate- parent effects. Unlike Schmalensee (1985), Rumelt (1991) found that corporate-parent effects contributed to variance, although Rumelt (1991) concluded that the corporate-parent effect was small based on his components-of-variance result. Rumelt's (1991) ANOVA, reproduced in Column (3), received little attention at first partly because the discussion in Rumelt's (1991) paper highlighted the methodology that was directly comparable to Schmalensee (1985): the components-of-variance approach. Schmalensee's (1985) and Rumelt's (1991) studies raised several questions about data and method. First, some researchers expressed concern about the gen- erality of the results because the period of study- the mid-1970s-coincided with unusual macroeco- nomic conditions that might have affected industry, corporate-parent, and business-specific performance. MANAGEMENT SCIENCE/Vol. 48, No. 7, July 2002 836 This content downloaded from 146.155.94.33 on Mon, 20 Feb 2017 03:43:41 UTC All use subject to http://about.jstor.org/terms McGAHAN AND PORTER Variance in Accounting Profitability Second, Schmalensee (1985) reported that industry effects accounted for about 20% of variance in profits, whereas Rumelt (1991) reported that stable indus- try effects accounted for only about 8% of variance. Rumelt's (1991) specification also included a transient industry effect. The difference in result and in specifi- cation fueled some controversy about the true impor- tance of industry to differences in accounting profit, although Rumelt's (1991) specification of industry effects received less attention than merited by the importance of the results. Third, the absence of impor- tant corporate-parent effects suggested that corporate headquarters might not contribute to the performance of business units. Concern about the result was com- pounded by confusion about definition and measure- ment. Fourth, the results covered only manufactur- ers, which raised questions about the generality of the results to other sectors. Last, concerns were raised that transient corporate-parent or business-specific effects might be important,4 that serial correlation may have complicated the results, and that the reported results may have been sensitive to outliers and thus not rep- resentative (see Brush and Bromiley 1997).5 Recent studies by Roquebert et al. (1996) and McGahan and Porter (1997a) addressed a number of the questions raised by the previous studies. Both studies relied on a much broader dataset-the Com- pustat Business-Segment Reports. Compustat con- tains data on the accounting profitability of corpo- rations that are publicly traded on United States exchanges by four-digit SIC category. Each four-digit category for a firm is called a "business segment."6 Roquebert et al. (1996) used the Compustat reports for the 7-year period from 1985-1991. McGahan and Porter (1997a) used the reports for the 14-year period from 1981-1994. 4Rumelt's (1991) specification had included a transient industry effect, but not a transient corporate-parent or business-specific effect. Thus, transient industry effects may have acted as proxies for transient corporate-parent or business-specific effects. 5Brush and Bromiley (1997) used simulation analysis to show that the decomposition of variance is sensitive to the presence of outliers. 6 Analysis suggests that business segments are considerably larger than operating business units on average, although the data are also substantially disaggregated from the corporate level for diversified firms (see McGahanand Porter 1997a). These studies confirmed the presence of significant industry effects in the manufacturing sector during the 1980s and early 1990s, showing that earlier results had not been an artifact of unusual macroeconomic conditions in the mid-1970s. Roquebert et al. (1996) argued that since the sum of Rumelt's (1991) stable and transient industry effects (from his components- of-variance analysis) are comparable to the indus- try effects in Schmalensee (1985), there was no dis- crepancy in the importance of industry between Schmalensee (1985) and Rumelt (1991).7 Thus, the studies largely resolved questions about the impor- tance of industry to manufacturers. Both Roquebert et al. (1996) and McGahan and Porter (1997a) found evidence of corporate-parent effects among the business segments in the Compu- stat data. Using components-of-variance techniques, McGahan and Porter (1997a) found that corporate- parent effects accounted for 4% of the variance in profits over the 14-year period covered in the study. Segments of both diversified and undiversified firms were included in the analysis, with the corporate- parent effect held to zero for single-segment firms. The study by Roquebert et al. (1996) was restricted to manufacturing. The authors reported that corporate- parent effects accounted for 17.9% of variance among manufacturing segments over the 7-year period from 1985-1991. The authors attributed the difference with Rumelt (1991) to shifts in opportunities for corpo- rate parents between the mid-1970s and the mid- 1980s. However, the Roquebert et al. (1996) data also included only those corporations reporting on at least two segments. Estimates of the influence of indus- try, for example, were based on the performance of only diversified industry members.8 Only about half 7 Indeed, Rumelt (1991) had also made this point. Roquebert et al. (1996) also discuss a supplemental approach used by Schmalensee (1985) to study variance in industry-average profitability. 8 Table 2 in Roquebert et al. (1996) suggests that the authors did not screen their dataset to exclude four-digit SIC categories identified as "not elsewhere classified," and "miscellaneous." Because these categories typically contain segments that are not related in busi- ness practice, there is no economic or strategic basis for an industry effect. Thus, the inclusion of these four-digit SIC categories may diminish the importance of industry in their results independently of any distortion associated with the inclusion of only diversified firms. MANAGEMENT SCIENCE/Vol. 48, No. 7, July 2002 837 This content downloaded from 146.155.94.33 on Mon, 20 Feb 2017 03:43:41 UTC All use subject to http://about.jstor.org/terms McGAHAN AND PORTER Variance in Accounting Profitability of industry members in the Compustat Business- Segment data belong to diversified corporations, and diversified companies tend to perform differently on average than nondiversified competitors. This choice to exclude data on a large number of companies sig- nificantly distorted the Roquebert et al. (1996) results on both industry and corporate-parent effects. McGahan and Porter (1997a) also expanded the analysis beyond manufacturing, and included all sec- tors of the economy except government and finance. The results indicated strong differences in the impor- tance of effects by sector. In manufacturing, the influ- ence of industry and corporate-parent effects was lower than in any other sector, and, of business- specific effects, was higher. Finally, McGahan and Porter (1997a) also addressed several methodological issues. Rumelt's (1991) model included a term representing industry-year interac- tions. McGahan and Porter (1997a) argued that the term might proxy for interactions in the other types of effects and modeled a general first-order autoregres- sive process on the error term. By running Rumelt's (1991) model on manufacturing data, McGahan and Porter (1997a) were able to reconcile results of the two studies. With regard to method, McGahan and Porter (1997a) decomposed variance using both components- of-variance and nested ANOVA techniques. The core result, obtained using the COV method, indicated that year, industry, corporate-parent, and business-specific effects accounted for 2%, 19%, 4%, and 32%, respec- tively, of variance. The nested ANOVA indicated that the effects explained 0.3%, 7%-9%, 9%-12%, and 35%, respectively, of variance. These differences sug- gested the need for further research on the restrictive assumptions inherent in the COV and nested ANOVA methods. Seen as a whole, this body of research left a num- ber of questions unanswered. First, the recent stud- ies compound methodological questions because of the difference between COV and nested ANOVA results. The components-of-variance approach, dis- cussed extensively in both previous papers, does not generate estimates of each effect, but uses sum- mary statistics to assess the influence of variance in year, industry, business-specific, and corporate- parent effects. The approach requires the assump- tion that each of the effects on a particular business is drawn independently of the others. Similarly, the nested ANOVA approach does not model covari- ance between effects. The strong covariance between industry and corporate-parent effects reported in McGahan and Porter (1997a) suggests flaws in the assumptions required under both approaches. Here, we employ a simultaneous ANOVA imple- mented using regression analysis. The simultaneous ANOVA allows for a full set of covariance effects but does not assume randomness in the model errors. In particular, we have not imposed an assumption that the dispersion of business-segment effects around an industry mean is unrelated to the industry mean. In previous studies, the methods either assumed that the effects and their covariances were randomly generated or imputed all of the covariance either to the industry or to the corporate-parent effects. In some of the papers, the imputation of covari- ance to industry or corporate-parent effects was an artifact of reporting: Nested-ANOVA tables partly obscure the relative influence of each set of effects on the total variance. The covariance between industry and corporate-parent effects is potentially important because, for example, a diversified firm may be more likely to expand into particular types of industries. Thus, the main difference between our model and those in previous studies is that it reveals the incre- mental contribution to explanatory power of the cor- porate and industry effects while allowing for rela- tionships in the processes that generate the effects. This is possible because we estimate each of our mod- els separately using fixed-effects techniques that allow for covariance. The model allows us to address the implications of Brush and Bromiley's (1997) study about the sensitivity to outliers by reporting the dis- tribution of the dependent variable and the results of alternative specifications to serial correlation.9 9 Note that we report the rate of serial correlation in the unmod- elled error term in our report of results on each specification. We do not impose any structure on the process that generates serial correlation. In particular, we do not model interactions between the various classes of effects directly. Our study does not address one criticism in Brush and Bromiley (1997). Brush and Bromiley (1997) argue that the decomposition of variance-through any technique-involves dealing with the sum of squared differences and thus involves "nonlinear" treatment of outliers. We take the MANAGEMENT SCIENCE/Vol. 48, No. 7, July 2002 838 This content downloaded from 146.155.94.33 on Mon, 20 Feb 2017 03:43:41 UTC All use subject to http://about.jstor.org/terms McGAHAN AND PORTER Variance in Accounting ProfitabilitySecond, McGahan and Porter (1997a) found that the importance of effects in manufacturing did not broadly represent the importance in other sectors of the economy. In this study, we replicate the simultane- ous ANOVA for manufacturers to test the robustness of this finding. This analysis also controls for part of the differences with Roquebert et al. (1996), who stud- ied only manufacturers. The result is important for distinguishing whether broad conclusions from the studies on manufacturers are relevant for companies in other sectors. Finally, Roquebert et al. (1996) and McGahan and Porter (1997a) came to radically different conclusions about the importance of corporate-parent effects to variance in profitability. In this paper, we address the difference by analyzing how the inclusion of only diversified firms in Roquebert et al.'s (1996) analy- sis affected results.10 A replication for the diversified firms in manufacturing largely reconciles McGahan and Porter (1997a) with Roquebert et al. (1996). The comparison nonetheless exposes deeper limitations in the entire line of work about the corporate-parent effect. 3. The Model and Data The analysis relies on the following model of business-specific accounting profit: ri,k, t = A + yt + i + k + i, k + i, k, t (1) In this equation, ri k, t is the accounting profit in year t of corporate-parent k's business unit in industry i. Profit is the ratio of operating income to identifiable assets in percent. The right-hand-side variables are ,u, the economic average profit over the entire period; yt, the premium associated with year t; ai, the premium associated with participation in industry i; /k, the premium conferred by membership in a diversified view that variance is well established as an important statistic for describing a population, and that this type of research is comple- mentary to other types of theoretical and empirical work on firm performance. 10 In an earlier study based on a COV analysis on the same sec- toral data (McGahan and Porter 1997a), we argued that the indus- try, corporate-parent, and business-specific effects in manufacturing firms differed from effects on performance in other sectors. corporate-parent k in year t; i, k, the premium asso- ciated with business segment i, k given the presence of all of the other effects; and si, k, t the residual. We allow for first-order serial correlation in the residu- als and report the rate of serial correlation with our results. This model is estimated using dummy vari- ables to represent classes of effects. In the model, corporate-parent effects are defined to arise only if a corporation belongs to more than one included segment. We adopt this convention because the corporate-parent and the business-segment effect cannot be separated for firms that participate in just one segment. For undiversified firms, the corporate- parent effect is assumed to be zero. Thus, a mod- eled corporate-parent effect reflects the tendency of a firm's business segments to perform differently from the average given the industries in which the firm participates. Rather than report the thousands of coefficients estimated for the full model, results are presented in the form of an ANOVA in which each class of effects is restricted.1 Rates of serial correlation in the error term are presented for the full model and for each restricted model. When the model is restricted to omit one of the classes of effects, then rates of serial cor- relation are higher because the residual captures the omitted effects. Year effects are defined to capture the general impact of macroeconomic fluctuations in business activity, and are therefore restricted to be equal for all segments. When an industry or corporate- parent effect is omitted from the full model, the business-specific effect picks up the variation that would have been ascribed to the industry or to the corporate-parent effect. The importance of industry and corporate-parent effects is evaluated by assessing 1 The estimation procedure accounts for imbalance in the panel. Imbalance arises because of entry and exit into the Compustat data by various segments. Note that entry and exit from Compustat does not necessarily constitute actual entry and exit from the economy (see McGahan and Porter 1997a). To deal with imbalance, we gener- ated, calculated, and inverted the matrix implied by our regression equation using new software designed for large, sparse matrices by MATLAB. Thanks to Arthur Schleifer for extensive discussions regarding this process. MANAGEMENT SCIENCE/Vol. 48, No. 7, July 2002 839 This content downloaded from 146.155.94.33 on Mon, 20 Feb 2017 03:43:41 UTC All use subject to http://about.jstor.org/terms McGAHAN AND PORTER Variance in Accounting Profitability their explanatory power in models that exclude business-specific effects.12 To explore the results for manufacturers, we iden- tify manufacturing segments based on the first digit of the SIC codes (we consider businesses classified in SICs from 3000-3999 to be manufacturers). A subtle question arises with regard to identification of diver- sified corporate parents. For the aggregate analysis, diversified corporate parents are identified as corpo- rations with two or more segments in the dataset. In their replication of results by economic sector, McGahan and Porter (1997a) reclassify corporations within specific sectors. For example, corporations in the manufacturing sector are considered diversified only if they include two or more manufacturing segments. The purpose of this classification was to make the results comparable to Schmalensee (1985) and Rumelt (1991). For consistency with the previous studies (including Roquebert et al. 1996), this analysis 12The nature of an ANOVA involves examining the incremental explanatory power of a specific set of effects and, hence, there is an inherent "nesting" quality to an ANOVA. There is no difference in the estimation procedure between the simultaneous ANOVA and nested ANOVA when business-specific effects are introduced into the model. The reason is technical: Business-specific effects are linear by design with both the industry and the corporate- parent effects. This occurs because the industry effect is numerically equivalent to the average of business-specific profits among indus- try members; similarly, the corporate-parent effect is equivalent to the average of business-specific profits among corporate members. There is a subtle difference between the simultaneous ANOVA and the nested ANOVA, however, in the models that incorporate the industry and corporate-parent effects. Industry and corporate- parent effects are not linear by design, and there may be covariance between the effects in the data. The nested ANOVA approaches impute all of the covariance to the first introduced effect. By esti- mating a simultaneous model that includes both industry and corporate-parent effects and comparing the results with models that include either industry or corporate-parent effects, we can bet- ter understand whether relationships between the industry and corporate-parent effects influence the results. The components-of- variance models often generate estimates of the covariance between the industry and corporate effects, but under an unusual assump- tion: COV models assume that the covariances as well as the effects are randomly generated. Thus, the approach does not account for systematic relationships such as the tendency of high-performance industries to host a disproportionate number of diversified firms. This understanding is crucial for establishing the importance of industry and corporate-parent influences on performance. treats corporations as diversified, based on their num- bers of segments within the manufacturing sector. The data come from the Compustat Business- Segment reports,which include information on com- panies with equity that is publicly traded in American markets. For each corporate parent, the Compustat reports identify up to 10 lines of business. Each line is identified by a segment number, which allows track- ing of performance between years even if the name or primary SIC of the segment changed. Companies are allowed to adopt reasonable conventions for allo- cating operating income and assets to particular seg- ments, with segment results included in the com- pany's audited financial statements.13 The Compustat database was screened as in McGahan and Porter (1997a).14 We excluded about 15% of the original observations because they belonged to four-digit categories that do not cor- respond to economically meaningful industries (i.e., "not elsewhere classified," etc.). Segments in such categories are often not direct rivals, and including them would understate industry effects and over- state business-specific effects. Following Schmalensee (1985) and Rumelt (1991), we also excluded segments with less than $10 million in sales or assets because they are often created for the disposition of assets prior to exit, for example. Segments that are the only organizations within an SIC (analogous to monop- olies) are omitted because a business-specific effect 13 We used Compustat's conventions for dealing with the SIC revi- sions that took place in 1981, 1987, and 1992. 14 None of our screens on data involved an exclusion based on the dependent variable, as in Roquebert et al. (1996). Before screen- ing, the dataset contained 151,929 records, each of which con- tained information on a single business segment in a particular year between 1981 and 1994. From this dataset, we dropped 2,743 records that do not contain a primary SIC designation. A total of 22,041 records were excluded because they are in SICs identified as "not elsewhere classified," "nonclassifiable establishments," or "government, excluding finance." We also dropped 15,689 records on "depository institutions" and 2,529 records on the only organiza- tions in their primary SIC classifications in specific years (analogous to monopolies). Another 1,433 observations were excluded because they were associated with segments that were in the database for only one year. We then excluded 29,077 very small segments with less than $10 million in sales and an additional 5,675 segments with less than $10 million in assets. MANAGEMENT SCIENCE/Vo1. 48, No. 7, July 2002 840 This content downloaded from 146.155.94.33 on Mon, 20 Feb 2017 03:43:41 UTC All use subject to http://about.jstor.org/terms McGAHAN AND PORTER Variance in Accounting Profitability Table 2 Average Profitability of Business Segments Avg. Assets Avg. Assets No. ($mil) Avg. Profita Median Profit No. ($mil) Avg. Profita Median Profit All yrs 72,742 829 10.2 9.8 1981 4,643 507 14.3 12.6 1988 5,112 865 10.4 9.9 1982 5,200 528 11.3 10.9 1989 5,030 948 9.8 9.4 1983 5,285 556 11.4 10.8 1990 5,029 1,028 9.5 9.0 1984 5,205 598 11.9 11.6 1991 5,114 1,040 8.4 8.4 1985 5,195 660 10.3 10.3 1992 5,232 1,051 9.0 8.7 1986 5,249 699 9.2 10.0 1993 5,396 1,127 9.1 8.7 1987 5,319 772 10.0 9.8 1994 5,733 1,161 9.1 9.0 Note. aAverage ratio in percent of operating income to identifiable assets. cannot be distinguished from an industry effect. Roquebert et al. (1996) report that their analysis encompasses 746 different four-digit SIC categories with designations between 2000-3999 (manufactur- ing). In our data, after exclusions, we report on 390 different four-digit SIC categories with comparable designations between 2000-3999. Thus, the finding of lower industry influence in Roquebert et al. (1996) may be at least partly attributable to this difference. Our screened dataset includes 72,742 observations for an average of 5,196 per year.15 The dataset rep- resents the activities of 13,660 distinct business seg- ments in a total of 668 different industries, which are represented by their four-digit SIC codes. The aver- age business segment posts 5.3 years of data, a period somewhat longer than the 4 years covered by Rumelt (1991).16 Each industry in each year includes the activ- ities of 10.1 business segments on average. We have information on 7,793 corporations, with 1,943 partic- ipating in more than one industry in at least one year. In years of diversification, these corporations 5Outliers are omitted as we drop observations in the screening process. In particular, we drop data on three reports of extraor- dinarily high return on assets among a group of oil-and-gas- exploration companies that have moderate amounts of income but hardly any assets (i.e., less than $1 million in assets). Note that at no point do we screen on the dependent variable, however. After the screens, the resulting distribution on the dependent variable is sta- tistically indistinguishable from normal. Thanks to Arthur Schleifer for extensive discussions to verify the screening process. 16 The lengthening of the series tends to depress the stable portions of the effects and to increase the transient portions of the effects. If the time series were long enough, then all stable effects would be eliminated. post information on 2.8 business segments on aver- age. As a result, 47.8% of observations are associated with diversified firms. The mean profit (expressed as the ratio of operating income to identifiable assets) is 10.2% with a variance of 260%. Table 2 shows the yearly number of observations, average size in assets, average profit, and median profit. The typical business segment, with assets of $829 million, is considerably larger than an operating busi- ness unit.17 There are several implications for our results. It is likely that a typical Compustat segment reflects actual operating activity in three or four SIC codes (at the four-digit level). As a consequence, the operations posted to each SIC in the Compustat data are probably more diverse than the actual operations in each SIC. The broadening of industry definition beyond the real four-digit level probably dampens industry and corporate-parent effects in our results. (Corporate-parent effects will be dampened if the typ- ical parent participates in a greater variety of indus- tries than reported in the segment data.) These prob- lems are exacerbated because the SIC system does not map closely to actual economic activity in some sec- tors, particularly the computing and medical device industries. As a result, we interpret our results cau- tiously. A finding of high business-specific effects with low industry and low corporate-parent effects may reflect artificial aggregation in Compustat rather 17 Roquebert et al. (1996) describe Compustat Business Segments as "SBUs," or strategic business units. We believe that this represen- tation is somewhat misleading. MANAGEMENT SCIENCE/Vol. 48, No. 7, July 2002 841 This content downloaded from 146.155.94.33 on Mon, 20 Feb 2017 03:43:41 UTC All use subject to http://about.jstor.org/terms McGAHAN AND PORTER Variance in Accounting Profitability than real differences in economic activity. This prob- lem is fundamentally related to general questions of appropriate industry definition.18 There are several advantages of our data. First, the 14-year time series allows us to identify effects that are truly stable over a long period. (The longer time series tends to depress our estimates of stable effects compared to Rumelt's four-year time series and the Roquebert et al. (1996) seven-year series, however.) Second, the period we study spans several phases of the business cycle. We also provide a benchmark for prior results on the period immediately follow- ing the first oil shock. Third, Compustat captures a large portion of activity in all sectors of the American economy. Business segments in the raw Compustat Business Segment data (afterscreening only for miss- ing observations and for financial firms) account for about two-thirds of the corporate sales and 45% of the corporate assets reported to the Internal Revenue Service for nonfinancial sectors from 1985-1992, the last year for which data is available. After the appli- cation of our screens, the data covers slightly more than half of corporate sales and slightly more than a quarter of corporate assets in nonfinancial sectors. Schmalensee (1985) reports that the FTC data in his study accounted for about half of manufacturing sales and two-thirds of manufacturing assets in 1975. 4. Are Results Robust to Analytical Method? The first outstanding question raised by recent stud- ies is whether results are robust to analytical method. In this section, we show the results of a simultane- ous ANOVA approach for Equation (1) in compar- ison with the results for a variety of related mod- els where restrictions have been imposed. We also show the incremental explanatory power associated with year, industry, corporate-parent, and business- specific effects, respectively, and show the robust- ness of results to serial correlation. If the results are similar to those of the previous studies, then we have evidence that the entire body of work is robust 18 Chang and Singh (2000) find that their results on market share are closely related to the narrowness of industry definition. to method. If the results are dissimilar, then addi- tional research is needed either to find the definitive methodology or to reconcile the approaches. The results of our analysis-of-variance on Equa- tion (1) are shown in Figure 1, which is broadly com- parable to Figure 1 in Schmalensee (1985). The model at the bottom of the figure corresponds to the fully specified model in Equation (1). All other entries in Figure 1 correspond to model in which at least one class of effects is restricted to zero. The serial corre- lation in residuals (p), and the ordinary and adjusted R2 are shown for each model. Each line is accompa- nied by the probability at which an F-test rejects the corresponding restriction. Consider first the fully specified model at the bot- tom of the figure. Each of the lines immediately above this model points to a model in which one type of effect is omitted.19 The first two of these lines are associated with restrictions on corporate- parent and industry effects, respectively. In each case, the level of the F-test does not reject the restric- tion because industry and corporate-parent effects are linear by design with business-specific effects. The third line points to a model in which business-specific effects are restricted. The F-test rejects the exclusion with 1% confidence. Note that by comparing models we are invoking the inherent "nested" nature of an ANOVA. The description of our models as "simulta- neous" ANOVA derives from the fact that each model reported in the figure is estimated while accounting for covariance between the estimated effects. The next-highest group of lines corresponds to var- ious restrictions on models in which three of the four effects are present. The first group of three lines is associated with restrictions on the model that includes year, industry, and business-specific effects. The F-tests cannot reject the restriction on industry effects (because of linearity by design with business-specific effects), although they do reject restrictions on business-specific effects. Similarly, the second group of three lines is associated with restric- tions on the model that includes year, business- specific, and corporate-parent effects. The F-tests can- not reject the restriction on corporate-parent effects, 19 For simplicity, the chart does not depict the exclusion of year effects. Year effects are significant. MANAGEMENT SCIENCE/Vol. 48, No. 7, July 2002 842 This content downloaded from 146.155.94.33 on Mon, 20 Feb 2017 03:43:41 UTC All use subject to http://about.jstor.org/terms McGAHAN AND PORTER Variance in Accounting Profitability Figure 1 Analysis of Variance on Equation (1) Null Model >o^93^^ /^o.99 N^>0.9^ p>0.99 Year Effects Industry Effects Business-Specific Effects Corporate-Parent Effects est. p = 0.340 est. p = 0.299 est. p = 0.112 est. p = 0.231 R2= 0.008 R2= 0.095 R2= 0.591 R2= 0.160 adj. R2= 0.008 adj. R2= 0.078 adj. R2= 0.497 adj. R2= 0.135 Industry Effects Business-Specific Effects est. p = 0.297 est. p = 0.102 R2= 0.104 R2= 0.601 adj. R2 = 0.097 adj. R2 = 0.510 Year, Industry, & Year, Industry, & Business-Specific Effects Corporate-Parent Effects est. p = 0.102 est. p = 0.217 R2 = 0.601 R2 = 0.224 adj. R2= 0.501 adj. R2= 0.185 Corporate-Parent Effects est. p = 0.230 R2= 0.167 adj. R2= 0.141 Year, Business-Segment, & Corporate-Parent Effects est. p = 0.102 R2 = 0.601 0 Year, Industry, Business-Specific, & Corporate-Parent Effects est. p=0.102, R2= 0.601, adj. R2 = 0.510 Note. This figure shows the estimated rate of correlation, the R, and the adjusted R2 in models that include various sets of effects. Each line is accompanied by a figure that represents the probability with which the model rejects the restriction indicated by comparing the two models. For example, the model at the bottom of the figure includes year, industry, business-specific, and corporate-parent effects, and generates an R2 of 0.601. The model immediately above it excludes the business-specific effects, and generates an R2 of 0.224. The difference in the explanatory power of the two models is significant at the 99% level, as indicated by the "> 0.99" that accompanies the restriction. Thus, the analysis shows that business-specific effects add significant explanatory power even in a model that already includes year, industry, and corporate-parent effects. but can reject the restrictions on business-specific effects. These results provide additional support for business-specific effects. The third group of three lines is especially important because it is associated with restrictions on the model that includes year, indus- try, and corporate-parent effects, but not business- specific effects. Industry and corporate-parent effects significantly contribute to explanatory power when business-specific effects are excluded. These results support the inclusion of industry and corporate- parent effects. The third-highest group of lines corresponds to restrictions on models with two sets of effects. Business-specific effects have important explanatory power in the fixed-effects model. The remaining mod- els also reject the exclusion of all effects, except in MANAGEMENT SCIENCE/Vol. 48, No. 7, July 2002 843 This content downloaded from 146.155.94.33 on Mon, 20 Feb 2017 03:43:41 UTC All use subject to http://about.jstor.org/terms McGAHAN AND PORTER Variance in Accounting Profitability the cases of linearity by design. The results also sug- gest relationships between industry and corporate- parent effects. Adjusted R2 drops by a relatively small amount when either industry or corporate-parent effects are removed from the model with year, indus- try, and corporate-parent effects. The final group of restrictions at the top of the fig- ure provide information about the explanatory power of each type of effect on its own. When only one of the classes of effects is present, the F-statistic never rejects the restriction to the null model. In sum, Figure 1 confirms that all four types of effects-year, industry, corporate-parent, and business-specific-are justified for inclusion in the full model. Table 3 summarizes the results from Figure 1 on the increment to explanatory power by type of effect. To construct Table 3, we calculated the increment to the ordinary and adjusted R2 with effects introduced in the following order: year, industry, corporate-parent, and business-specific.20 Year effects add lessthan 1% to both ordinary and adjusted R2. Industry effects add 9%-10%, corporate-parent effects add 9%-12%, and business-specific effects add 33%-38%. Thus, business-specific effects are more important than any other type of effect. Industry and corporate-parent effects are about equally important, and year effects are relatively unimportant (although significant). Both industry and corporate-parent effects are comparable to those obtained in McGahan and Porter's (1997a) nested ANOVA. Thus, the findings in this literature generally prove robust and invariant to method. For each of the models, Figure 1 also reports the rate of serial correlation in residuals, p. For the full model, the rate of serial correlation is 10.2%. In restricted models, the rate of serial correlation is higher because the residuals include the omitted effects. In the full model, the rate of serial correlation represents the ten- dencies of shocks in a specific year to influence returns in the subsequent year. Because the effects of indus- try, the specific business, and the corporate parent are 20 If business-specific effects were introduced before industry and corporate-parent effects, then industry and corporate-parent effects would have no explanatory power because all profit differences in industries and in corporate parents would be previously captured in the business-specific effects. We judged that this order of intro- duction would be minimally informative. Table 3 Increment to Explanatory Power by Type of Effect Ordinary R2 Adjusted R2 Yeara 0.8% 0.8% Industryb 9.6 8.9 Corporate-parentc 12.0 8.8 Business-specificd 37.7 32.5 Full model 60.1 51.0 Notes. alncrement in model of year effects over null model. blncrement in model of year and industry effects over model of year effects. Clncrement in model of year, industry, and corporate-parent effects over model of year and industry effects. dincrement in full model over model of year, industry, and corporate-parent effects. defined to apply across the entire 14-year period, the serial correlation in the residuals reflects any shock with intertemporal influence greater than one year but less than the full 14-year period under study. Analysis of the residuals in estimation of both the fully spec- ified model and the model with year and business- specific effects yields no evidence of heteroscedasticity in either sales or assets. For the full model, the corre- lation between the residuals and the inverse of assets is 0.7%. Table 4 contains the results from models corrected for serial correlation.21 The first column shows the results from the uncorrected model for reference. The second column shows results when each of the con- stituent models (i.e., the model of year effects, the model of year and industry effects; the model of year, industry, and corporate-parent effects; and the full model with all effects) is corrected for its own esti- mated serial correlation. The estimates are substan- tially similar to those in the uncorrected model. This approach, which is standard for dealing with serial correlation, generates R2 that are based on different sums of squares because observations are corrected for different rates of serial correlation in each model. The results reported in the third column of Table 4 are based on the estimates generated by the standard 21 Previous studies-particularly McGahan and Porter (1997a)- dealt with the presence of serial correlation by stipulating a cor- rected model. In this paper, take a more general approach and show the robustness of results in models that are both uncorrected and corrected. MANAGEMENT SCIENCE/Vol. 48, No. 7, July 2002 844 This content downloaded from 146.155.94.33 on Mon, 20 Feb 2017 03:43:41 UTC All use subject to http://about.jstor.org/terms McGAHAN AND PORTER Variance in Accounting Profitability Table 4 Increment to Ordinary R2 by Type of Effect in Models Dealing with Serial Correlation Correction Uncorrected Standard on full model correction model Yeara 0.8 0.4 0.4 Industryb 9.6 9.2 10.3 Corporate-parentc 12.0 11.7 11.6 Business-specificd 37.7 39.3 36.0 Full model 60.1 60.6 58.3 Notes. alncrement in model of year effects over null model. bIncrement in model of year and industry effects over model of year effects. Clncrement in model of year, industry, and corporate-parent effects over model of year and industry effects. dincrement in full model over model of year, industry, and corporate-parent effects. serial correlation (from Column 2) and the total sums of squares on the uncorrected data. The R2 in the models of Column 3 are directly comparable with one another because the total sum of squares in each model is the same. The results are similar to those in the previous columns. In the subsequent sections of the paper, we use uncorrected models because they involve the simplest of assumptions. In cases where our results would differ substantially, we also report on models corrected for serial correlation. The analyses presented in Tables 3 and 4 resolve a central question regarding previous studies on vari- ance in business-segment accounting profit regarding the robustness of results to differences in method. Previous studies employed methods of analysis- namely, components-of-variance techniques and nested ANOVA-that required restrictive assump- tions about the absence of meaningful relationships between the economic processes generating year, industry, corporate-parent, and business-specific effects. As a result, estimates of the importance of corporate-parent effects differed substantially when the same data were analyzed using different statisti- cal approaches (see Rumelt 1991 and McGahan and Porter 1997a). The methodology on which the results are based allows for a full set of covariance effects, and generates results that are robust to serial corre- lation in the data. The comparison with McGahan and Porter (1997a) suggests that small differences in results obtained under different analytical methods should not be interpreted as meaningful. 5. Are Results for Manufacturers Representative? A second major issue in the literature on variance decomposition concerns whether the results of the early studies on manufacturers were representative. This question carries implications for future research because much more data is normally available on manufacturing companies than on firms in other sec- tors. If manufacturers are representative in the aggre- gate, then the results of detailed studies of manufac- turing may hold for a broader cross-section of firms. McGahan and Porter (1997a) suggested that the importance of industry, corporate-parent, and business-specific effects in manufacturing did not broadly represent the importance of effects among businesses in other sectors. This suggestion was based on comparison of a components-of-variance analysis of businesses in manufacturing with a components- of-variance analysis of businesses in other sectors of the economy. To test the robustness of this claim, we replicated results of our simultaneous ANOVA on the manufacturing segments in the screened Compustat dataset for 1981-1994. The results are presented in Table 5. The first two columns, labeled "uncorrected model" show the results under the simple assump- tions of regression analysis without correction for serial correlation. The decomposition of variance for manufacturers is shown in the first column and the decomposition for all of the covered sectors is shown in the second column. The results for the influence of corporate-parent effects are the same, although the influence of industry and business-specific effects differs somewhat. The columns labeled "standard correction" and "correction on the full model" show the analyses corrected for serial correlation in the same manner as in the previous section.The results on corporate-parent effects are similar for manufac- turers and for businesses in all of the covered sectors, although the results on the influence of industry differ in the corrected models. Table 5 supports McGahan and Porter's (1997a) earlier claim on the importance of sectoral analysis, MANAGEMENT SCIENCE/Vol. 48, No. 7, July 2002 845 This content downloaded from 146.155.94.33 on Mon, 20 Feb 2017 03:43:41 UTC All use subject to http://about.jstor.org/terms McGAHAN AND PORTER Variance in Accounting Profitability Table 5 Incremental Contribution to Ordinary R2 for Manufacturers Correction on Uncorrected model Std. correction full model (1) (2) (3) (4) (5) (6) Mfg. All Mfg. All Mfg. All Yeara 1.1 0.8 0.7 0.4 0.6 0.4 Industryb 7.1 9.6 6.9 9.2 7.6 10.3 Corporate-parentc 12.0 12.0 11.0 11.7 10.8 11.6 Business-specificd 35.2 37.7 38.7 39.3 35.1 36.0 Model 55.4 60.1 57.2 60.6 54.1 58.3 Error 44.6 39.9 42.8 39.4 45.9 41.7 Total 100.0 100.0 100.0 100.0 100.0 100.0 Estimated serial correlation 0.165 0.102 Notes. alncrement in model of year effects over null model. blncrement in model of year and industry effects over model of year effects. Clncrement in model of year, industry, and corporate-parent effects over model of year and industry effects. dlncrement in full model over model of year, industry, and corporate-parent effects. although the results are somewhat different than the COV. Components-of-variance techniques, which do not allow for relationships in the processes that gen- erate industry and corporate-parent effects, detected no influence of the corporate parent within manufac- turing. In contrast, the simultaneous ANOVA detects corporate-parent effects among manufacturers that are similar to those that arise for businesses in all sectors. The COV technique did identify differences in the importance of industry for manufacturers and firms in other sectors, however. The simultaneous ANOVA in Table 5 reveals that the idiosyncratic portion of profits for manufacturers (captured in the residual) persists at a higher rate in manufacturing than in other sectors. When models are corrected for serial correlation, industry effects are affected significantly. Thus, manufacturing is not rep- resentative both because the magnitude of effects is somewhat different, but also because the correction for serial correlation suggests different rates of persis- tence for manufacturers and for businesses in other sectors. 6. How Important Are Corporate-Parent Effects? Perhaps the greatest controversy arising in this research regards the robustness of findings about corporate-parent effects. Some authors have sug- gested that corporate-parent effects are much more important than most of the studies suggest. In par- ticular, a recent study by Roquebert et al. (1996) sug- gests that corporate-parent effects account for a large part (17.9%) of variance in the accounting profit of manufacturers covered in the Compustat Reports for 1985-1991. This result conflicts with the results from McGahan and Porter (1997a) and with results of the current study that indicate a smaller corporate-parent influence. Table 6 reconciles the difference between Roquebert et al. (1996) and this study. The first four columns of Table 6 show the results of a standard ANOVA on all sectors. The first column is a reproduction of results from Table 3 for reference. The second through fourth columns replicate results for 1985-1991, the period covered in Roquebert et al. (1996). A com- parison between the first and second columns indi- cates that industry, corporate-parent, and business- specific effects explain somewhat more of variance in profitability during the 7-year period from 1985-1991 than during the full 14-year period from 1981-1994. This result is fully consistent with the idea that the effects dissipate and change over time, thus dimin- ishing their contribution to variance over a longer period. MANAGEMENT SCIENCE/Vol. 48, No. 7, July 2002 846 This content downloaded from 146.155.94.33 on Mon, 20 Feb 2017 03:43:41 UTC All use subject to http://about.jstor.org/terms McGAHAN AND PORTER Variance in Accounting Profitability Table 6 Models of Various Types with Corporate-Parent Effects (1) (2) (3) (4) (5) (6) (7) (8) Sectoral coverage All All All All Mfg. Mfg. Mfg. Mfg. Period of coverage 1981-1994 1985-1991 1985-1991 1985-1991 1981-1994 1985-1991 1985-1991 1985-1991 Corporate screens All All 2+ segs 3+ segs All All 2+ segs 3+ segs N 72,742 36,048 20,677 16,213 58,340 11,233 5,379 3,430 Yeara 0.8 0.2 0.3 0.4 1.1 0.2 0.5 0.5 Industryb 9.6 11.4 14.6 16.3 7.1 8.2 9.9 11.0 Corporate-parentc 12.0 14.2 19.5 17.8 12.0 13.7 23.7 17.1 Business-specificd 37.7 41.1 33.6 33.8 35.2 44.3 34.9 43.0 Full model 60.1 66.9 68.0 68.2 55.4 66.4 70.0 71.6 Notes. alncrement in model of year effects over null model. blncrement in model of year and industry effects over model of year effects. Clncrement in model of year, industry, and corporate-parent effects over model of year and industry effects. dlncrement in full model over model of year, industry, and corporate-parent effects. The third column of Table 6 shows results when the data is screened to include only corporations with two or more included segments, and the fourth column shows results when the data is screened to include only corporations with three or more included seg- ments. The screens substantially change estimates of both industry and corporate-parent effects.22 The esti- mated influence of corporate-parent effects is maxi- mized when the data are screened to include corpo- rations with two or more segments. The Columns 5-8 of Table 6 show the same anal- yses for manufacturers, thus facilitating comparison with Roquebert et al. (1996). Column 5 replicates the results from Table 5 for reference. The Columns 6-8 cover the variance in profits among manufacturers from 1985-1991. Again, the influence of the corporate- parent effect is maximized when the data is screened to include corporations with two or more segments. Indeed, the results in Column 8 of Table 6 indicate an even greater influence of corporate-parent effects (at 23.7%) than reported by Roquebert et al. (at 17.9%). There are two reasons why corporate-parent effects have maximal influence when the data is screened to include corporations with two or more segments. First, the corporate-parent effects are defined to be zero for undiversified firms. Undiversified firms account for 22 A test of equality in means rejects at the 1% level the hypothesis that the industry and corporate-parent effects are the same across all of the columns. about half of the observations in the screened Compu- stat data. All else equal, the exclusion of undiversified firms should about double the reported influence of corporate-parent effects. Second, diversified corporate parents with more than two segments have corporate- parent effects that are defined to reflect the common tendencies of a larger group of member segments. With an increase in the size of the group, the com- mon tendency tends to diminish (all else equal). Thus, corporate-parent effects explain a smaller portion of variance when the data is screened to include only firms with three and more segments, for example. Indeed, Roquebert et al. (1996) show that the influence of corporate parents consistently diminishes when the data on diversified firms is screened to include par- ents with greater numbers of segments. (Roquebert et al. 1996 do not report on the influence of corporate parents when undiversified firms are included.) Thus, differences between the results reported by Roquebert et al. (1996) and those reported in this study can be attributed to choices regarding screens on the data. The comparison also indicates impor- tant relationships between diversification and theesti- mated influence of industry and business-specific effects. In our view, the superior approach is to esti- mate the importance of year, industry, corporate- parent, and business-specific effects on a dataset that includes both undiversified and diversified firms. The exclusion of undiversified firms leads to spurious estimates of industry influence, for example, because MANAGEMENT SCIENCE/Vol. 48, No. 7, July 2002 847 This content downloaded from 146.155.94.33 on Mon, 20 Feb 2017 03:43:41 UTC All use subject to http://about.jstor.org/terms McGAHAN AND PORTER Variance in Accounting Profitability industry effects are imputed from the performance of only diversified members. The results in Table 6 suggest that diversified corporate parents have sys- tematically different industry and business-specific effects than undiversified firms. Furthermore, these systematic differences appear to differ for manufac- turing and other sectors of the economy. This anomaly deserves further research. 7. What Have We Learned? This stream of research based on the decomposi- tion of variance in accounting profitability leads to several important conclusions. First, business-specific effects are more important than year, industry, and corporate-parent effects in the variance of business- specific profitability. Year effects account for a small but significant portion of variance. Second, the rel- ative importance of year, industry, corporate-parent, and business-specific effects differs across sectors of the economy. Third, industry, corporate-parent, and business-specific effects are related in cross-section. For example, several of the studies show that indus- try and corporate-parent effects vary together. The choice of industry by diversifying corporate parents is related to industry performance, so that indus- try and corporate-parent effects are simultaneously determined. Fourth, industry, corporate-parent, and business-specific effects are related intertemporally.23 Businesses that perform differently from the aver- age in one year are likely to perform differently in the subsequent year. Persistence in performance may arise not just because of business-specific factors, but also from year, industry, or corporate-parent factors. For example, year effects persist if unusual perfor- mance in one year tends to yield to similarly unusual performance in the subsequent year. Additional studies using similar approaches are less likely to generate important new insights because they are limited technically, by data and by method. 23 The nature of the intertemporal link appears to vary by economic sector and by type of effect. Serial correlation in the idiosyncratic component of performance (i.e., the residual) is greater in manufac- turing than in other sectors. These results carry important implica- tions because they may reveal underlying patterns in the processes that generate the effects. The technical limitations originated at the incep- tion of the stream of research. The purpose of the studies was to identify the importance of indus- try, corporate-parent, and business influences with- out making claims about causality. The results not only confirm the importance of each of the effects, they also point to important relationships between the effects (i.e., to covariances between the sets of effects). Thus, in broad terms, the literature has also confirmed the limitations of the structure/conduct/performance models: There is evidence of feedback and coevo- lution between the industry, corporate-parent, and business-specific effects. Limitations of data arise from several sources. First, the SIC system includes very broad industry defi- nitions of at the four-digit level in some parts of the economy. As a result, the importance of indus- try is likely to be understated. Second, the Compu- stat data covers publicly traded firms and a large proportion of corporate revenue in the economy, but it does not include privately held firms. Any differ- ence in the performance of private firms would likely lead to increases in the portion of variance ascribed to industry and business-specific effects.24 Third, the studies use operating income as the measure of profit, and hence exclude extraordinary charges. In the early 1990s, companies under restructuring may have incurred significant extraordinary charges that are not reflected in the variance decomposition. If extraordinary charges reflect meaningful operational activity, then the importance of the various effects may be somewhat distorted. Limits on method also lead us to skepticism about the prospects for major new insights from research 24This would occur for two reasons. First, privately held firms often operate in single segments, for which corporate effects are defined as zero. Thus, any variation in their overall profitability is attributed to business-specific effects. Second, an analysis of data from the Internal Revenue Service's statistics on Business and Cor- porate Activity suggests that privately held firms arise more fre- quently in the lodging, entertainment, services, wholesale trade, and retail trade sectors than the publicly held firms. McGahan and Porter (1997a) have shown that industry effects are more important in these sectors than in others. Thus, we surmise that the inclusion of privately held firms would likely increase the importance of the industry effects. MANAGEMENT SCIENCE/Vol. 48, No. 7, July 2002 848 This content downloaded from 146.155.94.33 on Mon, 20 Feb 2017 03:43:41 UTC All use subject to http://about.jstor.org/terms McGAHAN AND PORTER Variance in Accounting Profitability using this approach. First, estimates of the influ- ence of year, industry, corporate-parent, and business- specific effects are obtained without exogenous infor- mation. Moreover, the methods do not support causal inferences about the determinants of accounting prof- itability because no structural variables are employed in the models. The method is limited because it is only descriptive. Second, the objective of the decomposition- namely, the variance in profitability-is defined to amplify the importance of outliers rather than obser- vations close to the norm.25 The technique therefore bases conclusions about the importance of year, indus- try, corporate-parent, and business-specific effects on the performance of outliers to a greater degree than normal observations. The method cannot yield refined conclusions about the relative importance of industry to incumbents with normal and usual profitability, for example. Third, the simultaneity in least-squares techniques may not be appropriate if the underlying economic processes do justify the restrictive assumptions of nested ANOVA. For example, consider the possibility that corporate-parent effects are shaped by opportu- nities related to industry structure. In this case, the proper economic model should attribute the portion of variance that is jointly determined by industry and corporate-parent effects to industry. The methodology of this study allocates the jointly determined vari- ance between industry and corporate-parent effects. Similarly, the technique does not identify the struc- tural relationships that may exist among industry and business-specific effects, and among corporate-parent and business-specific effects. Fourth, the corporate-parent effect is defined by common tendencies in the performance of a corpo- ration's segments. This definition may lead to some counterintuitive implications. For example, if the var- ious businesses of a corporation have similarly high profits, then a high corporate-parent effect will be registered even if the high profits were not specifi- cally attributable to intervention by corporate head- quarters. Conversely, the method does not fully cap- ture the influence of a corporate headquartersthat 25 This observation reflects Brush and Bromiley's (1997) criticism. intervenes to improve the performance of just a few member businesses. Defined in the particular manner adopted in this literature, then, the corporate-parent effect may have little relationship to the true economic influence of corporate headquarters.26 Last, business-segment effects are estimated in the variance decomposition from the stable portions of the residuals in a regression rather than by a set of structural variables. Thus, the problems of data that lower estimates of industry and corporate-parent influence also inflate estimates of business-specific influence.27 8. Where Do We Go from Here? Our analysis suggests several opportunities for extending the variance-decomposition literature. The limitations of the decomposition method are poten- tially mitigated by focusing on differences in the importance of effects within subpopulations. In McGahan and Porter (1997b, 1999), we show that the influence of industry and corporate-parent effects are substantially different for high and low performers, for example. The most direct opportunities for further research reside in exploring new data. Reliable and compara- ble data on the accounting profits of firms in other parts of the world would yield insight on ques- tions about the relationships between the national economic environment and industrial performance.28 Data on the profitability of privately held firms would provide results more representative of the entire econ- omy. Opportunities lie in exploring additional mea- sures of firm performance, including stock-market return and market share. Two studies (Wernerfelt and Montgomery 1988 and McGahan 1999a) decompose variance in Tobin's q and show that industry effects are as important as in the accounting-profit studies. 26 Bowman and Helfat (2001) expand on this point. 27 Technically, this would occur if the aggregate fixed effect on prof- itability were not affected (to the first order) by the diversity of four-digit activity reported for each segment. 28 Two studies in this spirit, Furman (1998) and Khanna and Rivkin (2001), show that the relative importance of the effects may differ radically in non-U.S. settings. MANAGEMENT SCIENCE/Vol. 48, No. 7, July 2002 849 This content downloaded from 146.155.94.33 on Mon, 20 Feb 2017 03:43:41 UTC All use subject to http://about.jstor.org/terms McGAHAN AND PORTER Variance in Accounting Profitability Chang and Singh (2000) decompose variance in mar- ket share and show the critical importance of industry definition. While there are ways to continue to learn from this research, its limits suggest that the time has come to explore whole new approaches. What might some of the new empirical strategies look like? One would be to identify cross-sectional relationships between the industry, corporate-parent, and business- specific effects. The variation of business-specific effects within an industry may be related to the aver- age performance of members (i.e., the industry effect), for example (see McGahan 1999b). Industry character- istics may be related to diversity in the performance of incumbents (see Rivkin 1997). Newly diversified corporate parents may have businesses with varied performance, whereas seasoned diversifiers may have similarly performing businesses. The propensity of a diversified firm to enter high-performing industries also may be related to the number of member busi- nesses. Investigation of these relationships will shed light on how attractive industries emerge. Additional research is also needed on the intertem- poral relationships embodied in effects. What kinds of changes in competitive position follow from shocks to industry structure? How long does it take for the changes to occur? Serial correlation revealed in the research so far suggests underlying links in the processes that generate the effects. McGahan and Porter (1997b, 1999) address the broad characteristics of these intertemporal processes, but do not exam- ine cross-sectional relationships in rates of serial cor- relation. It is no doubt true that both industry and business-specific effects emerge through interaction in the strategies of rivals over time. Entry by diversified firms affects the evolution of the target industry. Sim- ilarly, diversifying firms may be attracted to particu- lar kinds of industries. Studies on the decomposition of variance cannot address these issues because mod- els would be overspecified if interaction terms were included for industry-year, corporate-parent-year, and business-specific-year effects (see Rumelt 1991 and McGahan and Porter 1997a). More research on the interaction of effects over time will reveal important insights into the competitive process. Finally, detailed case studies at the sectoral level are needed to support deeper understanding of the processes that generate favorable and unfavorable effects at the industry, corporate-parent, and business- specific levels. In the chemical sector, for exam- ple, Lieberman (1987) shows how rivalry between direct competitors influenced the evolution of indus- try structure. Additional field research is necessary to understand the mechanisms by which corporate parents influence business segments. Such research may generate important new hypotheses for linking diversification with the structure of the originating industry or the competitive position of the originat- ing business unit, for example. New hypotheses about the connections between effects promise to open up a whole new level of statistical inquiry. In sum, our results indicate that major differ- ences between studies in the research stream can be reconciled. The literature's findings are generally robust. Industry and corporate-parent influences on firm profitability are related in complex ways to one another in cross section and over time. The robust findings suggest that the research has successfully shown that industry, corporate-parent, and business- specific influences are all important. New approaches are needed to understand how industry, corporate- parent, and business-specific influences interact. Acknowledgments The authors are grateful to two anonymous referees, Rebecca Hen- derson, Jan Rivkin, Richard Rumelt, Richard Schmalensee, par- ticipants in the NBER Productivity group, and attendees at the Academy of Management meetings for comments and discussions related to this paper. Special thanks to Arthur Schleifer for exten- sive discussions about statistical methods. Thanks to Todd Eckler, Dan Elfenbein, Lucia Marshall, Michael Susanto, Geoff Verter, Sarah Woolverton, and especially Jan Rivkin for help in compiling the data. The Division of Research at the Harvard Graduate School of Business Administration provided financial support for this project. The first author thanks the SRC and BUILDE at Boston University for generous research support. References Bowman, Edward H., Constance E. Helfat. 2001. Does corporate strategy matter? Strategic Management J. 22(1) 1-23. Bresnahan, Timothy F. 1989. Empirical studies of industries with market power. Richard Schmalensee, Robert D. 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