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Firms develop their organizational practices to realize returns from given and marketable resources. Implementing effective practices requires substantial up-front investment. We approximate the economic relevance of establishment-specific organizational capital by using a two-step procedure. First, we extract an establishment-specific performance differential from a within-panel estimator. Second, we explain the variation in this differential by using organizational and control variables. Our results make it possible for us to predict the contribution of organizational practices to the performance differential. We label this part of the firm-specific performance differential “organizational capital”. Our results indicate that organizational capital has a substantial impact on performance.
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SBR 61 October 2009 393412 393
Oliver Ludewig/Dieter Sadowski*
Measuring OrganizatiOnal Capital**
abs tr aCt
Firms develop their organizational practices to realize returns from given and market-
able resources. Implementing effective practices requires substantial up-front invest-
ment. We approximate the economic relevance of establishment-specific organizational
capital by using a two-step procedure. First, we extract an establishment-specific per-
formance differential from a within-panel estimator. Second, we explain the variation in
this differential by using organizational and control variables. Our results make it possi-
ble for us to predict the contribution of organizational practices to the performance dif-
ferential. We label this part of the firm-specific performance differential “organizational
capital”. Our results indicate that organizational capital has a substantial impact on per-
JEL-Classification: D24, L23, M29.
Keywords: Managerial Economics; Organizational Capital; Organizational Design;
Production Function.
1 Org ani zati Ona l Cap ital
Organizations develop their organizational practices to realize returns from given and
marketable resources like real capital and labor. Organizational practices that facilitate the
creation of sustainable above-average returns must be durable and idiosyncratic, i.e., hard
to imitate. In cases in which their implementation requires substantial investments, these
organizational practices, routines, and processes represent “organizational capital”.
e economics and management literature attaches different meanings to the term “orga-
nizational capital”. ere are at least two schools of thought. One views organizational
* Oliver Ludewig, Institute for Employment Research (IAB), Regensburger Straße 104, D-90478 Nürnberg.
Dieter Sadowski, Institute for Labour Law and Industrial Relationships in the European Community (IAAEG),
University of Trier, D-54286 Trier.
** We thank two anonymous referees, Douglas C. Bice, Ruslan Gurtoviy, Susanne Warning, and Dodo zu Knyphau-
sen-Aufseß as well as the participants of seminars, workshops and conferences at the universities of Zurich, Ha-
nover, Lima, and Munich. We greatly appreciate Sandra Sizer’s help to improve our English.
Electronic copy available at:
SBR 61 October 2009 393412
capital as residing in the organization’s members and their social networks (Prescott and
Visscher (1980)). e other ascribes organizational capital to the organization itself, not
to its members, considering it to be embodied in the company’s routines and practices
(Tomer (1986; 1987); Lev and Radhakrishnan (2005)). If we were to take this second
view to the extreme, then the stock of organizational capital would remain unchanged,
even if all employees were replaced.
To support the second viewpoint, which is our approach, we provide two examples:
If a whole football team is replaced, including the coach, but the playing strategy
and the performance stay unchanged, we can speculate that the organizational prac-
tices, such as their incentive or playing systems, are responsible for resulting in the
same outcome as before the replacement. ere is a famous example: Until the end
of the 1990s, Ajax Amsterdam applied the same playing system to all teams, from
the youngest junior team to the professionals. ere was always a pool of young,
motivated players who knew the system and could replace any injured or departing
player from the top team quickly and without any substantial loss in quality. It was
the system that made the difference, not the individual players. It was the base of
Ajax’s golden years.
During the 1990s, Wal-Mart was hailed as having successfully deployed information
and communication technology. However, this success was not because Wal-Mart had
exclusive access to special equipment linking the checkout registers directly with the
vendors. Rather, Wal-Mart’s use of this technology facilitated innovations in manage-
ment and organizational structure1. Wal-Mart’s competitors were slow to imitate this
use of freely available information and communication technology, giving Wal-Mart
a competitive advantage for quite some time.
In their 2005 study, Lev and Radhakrishnan state that “Organization capital is … an
agglomeration of technologies – business practices, processes and designs, ... – that
together enable some firms to consistently and efficiently extract from a given level of
physical and human resources a higher level of product than other firms find possible to
obtain.” Sadowski (2002) provides a similar, but more specific, definition: “If an enter-
prise succeeds in giving itself an order, including an amount of rules to share informa-
tion, settle conflicts, secure the willingness to cooperate, then we can call this order with
good reason ‘organizational capital’.” is idea holds for labor relations and for the rela-
tionships with other shareholders and stakeholders.
e metaphorical use of the term “capital” has a long and successful history. For example,
the concepts of establishment-specific and general human capital are basic in modern
economics, although they do not have a simple empirical correlate. From a firms perspec-
tive, “human capital” is the economic value of the knowledge and competencies of the
employees, deployed in favor of the firm.
1 Brynjolfsson, Hitt, and Yang (2002, 146); Lev and Radhakrishnan (2005); and Ramirez and Hachiya (2006b).
SBR 61 October 2009 393412 395
As far as social capital is concerned, Coleman (1988) states that it “[…] is created [...]
when the relations among persons change in ways that facilitate action.” Moreover, social
capital secures the flow of information, helps to coordinate actions, and facilitates coop-
eration (Matiaske (1999))2. us, human capital rests on the skills, knowledge, and abil-
ities of people, and social capital is based on individuals’ relationships with other persons
both inside and outside the firm.
If firms can benefit from the human and social capital of their personnel via purposeful
organizational practices, then such practices have a positive economic value and they
contribute also to “organizational capital” (Hardins 1999 concept of institutional capital is
analogous). Social capital, human capital, and organizational capital are linked, but theo-
retically separate. Bernd Schauenberg (1983) provided an early and thoughtful analysis of
these links; Bounfour (2009) shows how hard it still is to develop a metrics and statistical
reports to identify them empirically.
e research on organizational capital is closely connected to, and inspired by, the
resource-based view (Sadowski and Ludewig (2004); Schneider (2008)). In short, this
view states that strategic resources that generate a lasting competitive advantage have
to be scarce, hard to imitate, and hard to replace (Barney, Wright, and Ketchen (2001);
Knyphausen (1993)). ese conditions are fulfilled by many resources, especially those
that are intangible, such as human capital and social capital. Our interpretation of orga-
nizing as a company as a resource is related to the Dynamic Capabilities View, in which
organizational routines are the decisive resource that enables firms to survive in changed
environments better than their competitors (Teece, Pisano, and Shuen (1997)).
Organizational capital is as intangible as human and social capital. Organizational routines
are usually stable for intermediate time periods. Despite this stability, organizational capital
is exposed to the risk of becoming obsolete due to imitation or innovation of competi-
tors (Lev and Radhakrishnan (2005)). Only the part of organizational capital that cannot
be imitated can generate a sustainable competitive advantage. Organizational capital is
idiosyncratic and cannot be traded, unless the whole organization itself is sold (Black and
Lynch (2005)). erefore, there is no market price on organizational capital (Ramirez and
Hachiya (2006b)). Attempts to identify organizational capital must be closely linked to
its effects on profit, added value, or other performance measures.
We ask empirically what the importance is of the organizational capital of business units,
and which organizational practices generate a relatively lasting competitive advantage.
2 Meas ur e Me nt pr Obl eMs
We believe that organizational capital can explain why firms with identical resource
endowments differ in performance. Measuring the extent to which the performance of
2 Examples are obligations and favors that can be called on or information that can be obtained through these re-
SBR 61 October 2009 393412
establishments depends on their ability to organize their activities is obviously of both
practical and theoretical interest. We want to know in which way the different practices
contribute to the formation of organizational capital.
Accountants measure physical capital by its purchase costs minus depreciation. is
approach is not feasible for the measurement of organizational capital, because the acqui-
sition costs are not known. As noted above, it cannot be traded; therefore, it has no
market price (Black and Lynch (2005); Ramirez and Hachiya (2006b)). To a great extent,
the costs of organizational capital formation are opportunity costs, thus they are indirect
and hidden, and it is not possible to directly assess organizational capital by using acqui-
sition costs. But indirect approaches are also problematic. For example, subtracting the
book value of all its other assets from a firm’s market value isolates the value of organiza-
tional capital. However, this “goodwill” comprises not only the organizational capital, but
also all assets not accounted for in the balance sheet, including human and social capital
(Bresnahan (2005)).
ere is an additional obstacle to measuring the stock of organizational capital held
by any particular firm. It is difficult to decompose the organization’s performance at a
particular point in time into the different contributions of the corresponding assets, such
as real capital, labor, human capital, social capital, and organizational capital (Lev and
Radhakrishnan (2005)).
Instead, we measure the value of organizational capital by comparing the performance of
establishments with different organizational practices. We can either observe the same firm
across different points in time, or compare different organizations at the same point in time.
If they differ only in their organizational practices, then we can attribute the differences in
firm performance to their organizational differences. Such an indirect approach has impor-
tant consequences. First, instead of obtaining information about the total value of orga-
nizational capital, we will only know the differences in value caused by alternative sets of
practices. Second, because it is very unlikely that there are two identical firms that vary in
only a few organizational practices, econometric methods must control for other factors.
ere are many studies that apply such econometric approaches to determine the effects
of diverse organizational practices on performance. Only a few of these studies use the
concept of organizational capital. Others build on the ideas of “high performance work
practices” or “human resource management systems”. Although we could interpret their
results as measuring organizational capital, they fail to disentangle the effects of different
practices, because they use (additive) indices or dummy variables that indicate similar
organizational systems3. us, these studies assume that all practices contribute in the
same way to performance (Ludewig (2006))4. Further, they focus on human resources,
and do not account for other sources of organizational capital.
3 Examples of this type of Literature are MacDuffie (1995); Huselid, Jackson, and Schuler (1997); Ichniowski,
Shaw, and Prennushi (1997); Ludewig (2001).
4 These points are only shortcomings from the organizational capital perspective. However, the respective authors
have a human resource management view.
SBR 61 October 2009 393412 397
Atkeson and Kehoe (2005) use macro data to calculate the payments received by organi-
zational capital owners. ese payments are defined as the fraction of output that is not
accounted for by payments to labor, (physical) capital, and managers. ey estimate that
in the U.S.-manufacturing industry 4% of all payments go to the owners of organiza-
tional capital. According to their calculations this is more than 1/3 of the payments going
to owners of real capital.
Tomer (1981; 1987) suggests an approach similar to growth accounting models. A number
of recent papers (e.g. Lev and Radhakrishnan (2003); Ramirez and Hachiya (2006a;
2006b)) built on this idea. ey identify the (idiosyncratic) contributions of organiza
tional capital by analyzing the residuals of production function estimations (Schneider
(2008) provides an interesting overview of these efforts). However, these contributions
do not investigate which organizational practices explain the idiosyncratic performance
differentials, in other words, which practices contribute to organizational capital (Bres-
nahan (2005)).
3 Meas ur e Me nt O f Org ani zati Ona l Cap ital
We identify the establishment-specific performance differentials applying a production
function approach as well. We examine the plant or establishment level, because this level
is the locus of value-generating processes and decision making. In large corporations and
businesses, the different divisions have substantial discretionary leeway (Bartel (2004);
Schmitt (2002)). Bartel (2004) postulates that the performance measurement of organiza-
tional practices “[...] can only be done through detailed analysis at the plant level, [...].
We base our measurement method on the time structure of panel data. Such data makes
it possible to control and identify the “unobserved heterogeneity of single observations”,
i.e., the unobservable (or at least unobserved) establishment-specific characteristics that
might have a causal relation with the performance and that might be correlated with
other important variables. In conventional applications, such observation-specific effects
would bias the estimates if uncontrolled. ere are various techniques to implement such
However, our prime goal is not to control the establishment-specific effects, but to identify
and measure them. erefore, our first step is to estimate the establishment-specific effect
on performance. We do so by applying a within (fixed effect) estimator that bases the esti-
mation on differences between each variable and its average over time for each observa-
tion (Greene (2003)). We extract the fixed effect from the estimates.
Within a production function framework, this establishment-specific time fixed effect
reflects time-invariant output differentials between establishments. is establishment-
specific performance differential is in our interpretation and that of others (e.g., Lev and
Radhakrishnan (2003); Ramirez and Hachiya (2006a; 2006b)) generated to a substantial
extent by organizational capital.
SBR 61 October 2009 393412
In our second step we explain the establishment-specific contribution of organizational
capital to performance through organizational and personnel practices. Establishment-
specific output differentials serve as dependent variables, making it possible for us to
derive the contribution of different practices to organizational capital. Finally, we combine
the estimated model with establishment-specific variable values to predict individual estab-
lishment performance. We do not interpret the whole fixed effect as organizational capi-
tal’s impact on performance, because the establishment-specific part of the residual might
contain some unmeasured impact on performance (Bresnahan (2005)). Instead, we define
only that portion of the fixed effect as organizational capital that can be explained by orga-
nizational practices.
We augment the residual based approach in two ways. First, we control for the intangible
assets human capital and social capital. Second, we apply a two-step procedure in which
we decompose the establishment specific performance differential into the contributions
of organizational practices that constitute organizational capital.
4 est iMat iOn MOdel
In the first step of our two-step method, we assume a Cobb-Douglas production function,
which we amend with a term for organizational capital (Ω):
Qi,t =
β3 . (1)
Q denotes the output, K the capital stock and L the labor input of establishment i in
period t. e constant A represents overall efficiency.
To obtain a linear expression and to account for random measurement errors and
stochastic shocks, we take the natural logarithm and we add a random error εi,t:
lnQi,t = lnA + β1 lnΩi,t + β2 lnKi,t + β3 lnLi,t + εi,t. (2)
However, Ω is unknown. us, we must reformulate the model so as to approximate the
influence of an idiosyncratic and intangible resource on the outcome. Since we are only
interested in the idiosyncratic component of organizational capital, it is sufficient to derive
the establishment-specific variation of performance that is not explained by the remaining
factor endowment. Using a fixed effect approach similar to Lev and Radhakrishnan (2003)
or Ramirez and Hachiya (2006a; 2006b) yields:
lnQi,t = lnA + νi + β2 lnKi,t + β3 lnLi,t + εi,t, (3)
where ν
= β
lnΩ are the establishment-specific fixed effects. It gives the organizational
capital’s impact on Q. is positive (negative) impact shifts the base production function
AKβ 2Lβ3 outward (inward). As noted, we augment the basic function by using variables
for human capital and social capital.
SBR 61 October 2009 393412 399
e estimation procedure imposes the standard distributional assumptions of the esti-
mator on the fixed effect. erefore the average and median are around zero and there
are rather extreme values at both ends of the distribution. is distributional effect has
two important implications. First, that we must not interpret the absolute values derived
for establishments and their signs. e zero point is arbitrarily imposed by the estima-
tion procedure. e estimates are interval measures. Second, that we must account for the
distributional features in the second step estimation.
In our second step we use ν
as the dependent variable and regress it on organizational
practices, here summarized in the vector OrgVar:
νi = α0 + α1 OrgVari,t + µi,t. (4)
Equation (4) implies that time-variant variables explain the time-invariant variable νi.
Although we assume that organizational capital is to some extent time invariant, we do
not believe that it constant during the whole observation period, 1997-2005. It seems to
be more plausible to assume a stable organizational capital only for an intermediate time
interval (e.g., as do Lev and Radhakrishnan (2003)). Additionally, some of our core vari-
ables cover periods of two years. Due to the time structure of these variables, their possible
lagged effect on performance, and the expected intermediate durability of organizational
capital, we divide the total observation period into overlapping intervals of three years. We
apply the first step of our analysis to each of these intervals. We then assign the resulting
fixed effects for each interval to the respective establishments for the year in the middle of
the interval under consideration. Doing so yields equation (5):
νi,[t 1, t + 1] = α0 + α1 OrgVari,t + µi,t. (5)
We extract the establishment-specific performance differential for the year 2000 from
the fixed effects model that we apply to the interval 1999-2001. We obtain the impact
of organizational capital for the year 1998 from the first-step estimation of the inter-
vals 1997-1999, and so on. However, the data set covers several important variables that
affect organizational and personnel practices only in irregular intervals, so we cannot use
every possible three-year interval. Table 1 shows the four intervals that we can use for the
second step.
Table 1: Interval structure
First step interval of three years [t – 1, t + 1] Year assigned
1997, 1998, 1999 1998
1999, 2000, 2001 2000
2000, 2001, 2002 2001
2003, 2004, 2005 2004
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5 data
We use the IAB Establishment Panel (IAB-Betriebspanel; see Bellmann (1997) and Kölling
(2000) for details) as our database. is large-scale, general-purpose survey, which was
collected by the Institute for Employment Research (IAB), is a stratified random sample.
It is a longitudinal data set that provides information for annual waves from 1993 onward
for West Germany, and from 1996 for East Germany. It is primarily interviewer based,
but supplemented in some regions by mailed surveys that comprise identical question-
naires containing a broad range of variables regarded as important in economic theory.
e sample includes establishments companies of all sizes. ese basic structural elements
correspond to some of the principles of an ideal set of panel data suggested by Hamer-
mesh (1993). An establishment as it is comprised in the panel might be identical to the
entire firm or it might be the local division of a corporation.
Starting in 1993 with 4,300 units, the sample size of the survey was extended in several
steps and now covers almost 16,000 establishments. e sample firms are drawn from the
so-called Betriebsdatei of the Federal Labor Office. is database contains the base popu-
lation, which consists of all establishments with at least one employee who is covered by
the compulsory social security system. Over 80% of German establishments fulfill this
condition. e stratification of the sample implies a sampling probability that is increasing
with establishment size. Industry is the second sampling criterion.
Since the survey is supported by the German employers’ association and Federal Employ-
ment Agency (Bundesagentur für Arbeit), there is a response rate of around 70% for initial
contacts and about 80% for repeated contacts. e data provide general information on
the companies, such as organizational practices, total sales, employment, or the indus-
trial relations within the establishment. e IAB panel is unbalanced because of panel
mortality, the replacement of closed or nonresponding establishments and a more or less
continuous increase in sample size5.
e available data cover the period from 1993-2006. Due to some data restrictions, we
could use only the waves 1997 to 2005 for our first-step estimates. However, we also inte-
grate information from the 1995 and 2006 surveys, because some variables are defined
for previous as well as following years.
Because of nonresponse, panel mortality, and missing variable values, some firms generate
few observations, even over the whole observation period. We analyze only observations
that are not missing any values for the variables we use in estimation. We use only the
manufacturing sector. We exclude establishments with less than five employees, because
at this threshold legal requirements might influence organizational decisions. We use only
units with at least two observations. We end up with between 278 and 537 establish-
ments per three-year period, which gives us about 570 to 1,210 observations per obser-
vation period.
5 Hartmann and Kohaut (2000) show that the panel mortality, which contributes substantially to the unbalanced
nature of the panel, is not systematically correlated with corporate characteristics.
SBR 61 October 2009 393412 401
e panel has a core of questions that are repeated every year. ese questions address
general business development and strategy as well as personnel policies. Other issues are
raised biannually, triannually, or only once. By using the collected information, we can
check the impact of several organizational practices that might constitute organizational
capital, even though the set of practices is certainly not exhaustive.
First estimation step: dependent variable
Different studies that analyze the productive impact of organizational practices use several
measures to operationalize performance. e most prominent measure, the market value
of the firm, is in our view not feasible. First, given the current worldwide economic crisis,
it is questionable if financial markets are really providing correct estimates of firm values
(Bresnahan (2005)). Second, and even more important there are many firms that are not
listed in share markets. is observation is especially true in Germany (Vitols (2004))
Value added is available for most firms and it is strongly linked to the real value of a busi-
ness. erefore, we use value added as the dependent variable. Taking logarithms leads to
the exclusion of 27 observations.
First estimation step: explanatory and control variables
e IAB Establishment Panel does not directly gather information on the physical capital
stock. We approximate it by summing up the investment of the current and previous
year7. Investment is in many cases zero. us, we add one before taking the logarithm of
this variable to avoid drop outs. We approximate labor input by the logarithm of the total
number of employees.
We introduce proxy variables for the intangible human and social capital into our spec-
ification of the production function. ese variables are designed to indicate the impor-
tance of these intangible assets relative to the industry average. We derive a skill ration as
approximation of human capital. We calculate the average share of skilled employees on
a two-digit industry level (NACE equivalent) and divide the share of each firm by this
average. e resulting “skill ratio” gives us the industry-adjusted human capital intensity
of each company.
As discussed we include a proxy variable for social capital. We assume that a business that
relies on social capital must keep this capital within the establishment, so the firm must
aim at low quit rates. Based on this assumption, we put the relative rate of voluntary quits
into the function to control for the productive impact of social capital.
We also include the share of part-time employees in the production function. By doing
so, we can control for the effects of labor input variation due to differences in the number
of monthly working hours of employees. We must rely on this crude proxy because exact
working time of part-time employees is not collected in all waves.
6 Although there were about 2,445 public corporations in 1996, these were only 0.09% of all firms subject to VAT
(DAI (1999)). Additionally, only 802 of those firms were listed on a stock exchange (DAI (1999)). In 2001 there
were about 1,075 firms listed, with a total value of €1,200 billion, which corresponds to 60% of GDP. In the
U.S. and the UK, this relation was well above 100% (Vitols (2004)).
7 See for example Möller (2007), Bellmann and Büchel (2001), or Bellmann, Bender, and Schank (1999).
SBR 61 October 2009 393412
Second estimation step: dependent variable
We estimate the production function by using a fixed effects model for each of the inter-
vals given in Table 1. We extract the performance differential of each establishment by
predicting the added value of each unit by using the estimation results twice, first, by
making this prediction with fixed effects, then without. After taking the antilogarithm,
the establishment-specific performance differential is then the difference between these
two values. We calculate per capita values by dividing the performance differentials by
the number of employees (full-time equivalents). We perform this calculation for each
interval and assign the resulting values to the respective firms as described above. ese
fixed effects are centered, due to the distribution imposed on the residual. e fixed effects
represent the establishment-specific differences in value added per employee for a given
factor endowment. We analyze these differentials in the second step.
Second estimation step: explanatory and control variables
As we explained above, we propose that a substantial part of these establishment-specific
performance differentials is due to the differences in the firm’s ability to organize the
production process efficiently. It is this part of the fixed effect that we define as organiza-
tional capital. In our second step we estimate the contribution of specific organizational
practices to the performance differential.
e wage structure is one of the major influences on employee behavior. According to
the efficiency wage literature, a wage premium can improve productivity by, for example,
reducing shirking and increasing commitment8. e efficiency wage mechanism depends
on wages that are above the average market wages. We construct an industry-adjusted wage
ratio by dividing the average per capita wages at the firm level by the average industry per
capita wage. However, some researchers argue that high wages that are aimed at increasing
external motivation crowd out intrinsic motivation9. Consequently, the positive effect of
the wage premium may be offset by a negative effect, and the net effect is unknown.
In the German regulatory setting, the impact of works councils is ambiguous. e existence
of a works council can reflect a policy aimed at employee involvement which is expected
to increase performance. In contrast to other participatory practices (e.g., teamwork or
open-door policies) the works council is not under the discretion of management. e
existence of this institution depends on the willingness and effort of employees to establish
one (Addison et al. (2000)). If there is the willingness and the legally required minimum
number of five employees, workers have the right to establish a works council. Although
a works council can hardly be regarded as a managerial practice, managers can either
encourage or discourage its formation. Even if a council is formed despite management
resistance, it can support more cooperative candidates. To determine their empirical rele-
vance, we treat works councils as an organizational practice despite its ambiguous nature.
8 See for example Akerlof (1982); Shapiro and Stiglitz (1984); Groshen (1994); Stiglitz (1987).
9 See for example Osterloh and Frey (2000), Osterloh, Frey, and Frost (2001), Frey and Jegen (2001), Akerlof and
Kranton (2005; 2008), or Prendergast (2008).
SBR 61 October 2009 393412 403
One section of the IAB questionnaire examines firms’ organizational practices. A set of
dummy variables indicates the implementation of certain practices either at a specific
point in time or up to two years before. By using these variables we can create dummies
to distinguish whether or not these practices are implemented in the respective establish-
ment during the observation period. We note the presence or absence of the following
practices: quality control systems and quality circles (“quality control”), profit or cost
centers (“profit center”), teamwork (“teamwork”), delegation of decision-making power to
line workers (“empowerment”), and increased supply by external vendors or outsourcing
(“outsourcing”). us we cover a broad set of practices ranging from HRM (“empower-
ment” and “teamwork”) over controlling (“profit center”) to quality management covering
many dimensions of organizational capital.
We noted above that self-binding rules, such as job guarantees, can also enhance labor
productivity. erefore, we include the rate of layoffs in our estimation function. Again,
we relate the establishment level to the industry by dividing the establishment layoff rate
by the industry average. However, this variable might suffer from a problem of reversed
causality. It is unclear whether establishments have a better performance due to job guar-
antees or if they lay off fewer employees because of better performance. To avoid this
problem, we also include lagged values of this variable in our estimation function. Past
layoffs should not depend on current performance; however, a low number of layoffs
in the past still reflects a policy of job guarantees
. However, in economic crises layoffs
might reduce costs and raise net return in future periods. Following Schneider (2008),
we account for a U-shaped relation by inserting the (lagged) squared values of the relative
layoff rate as control variables into the estimation function.
Although information and communication technology (IT) is physical capital, it can have
a substantial impact on organizational structures and the outcome of organizational prac-
tices11. us, the efficient utilization of IT equipment can be a major source of organiza-
tional capital. In the second-step equation, we use a dummy that shows the influence of
IT investments in a given period12.
10 One might suspect that employer-generated layoffs and voluntary employee quits might be correlated. The cor-
relation coefficient for both variables is (highly) significant but very small, with values around 0.05. Thus, we
can ignore the co-movements of both variables.
11 See for example Black and Lynch (2005), Lev and Radhakrishnan (2005), or Brynjolfsson, Hitt, and Yang
12 Schneider (2008) is even using the presence of CNC-equipment in a company as a major indicator for organi-
zational capital.
SBR 61 October 2009 393412
We add 19 industry dummies
, which control for industry-specific circumstances such
as market structure, industrial relations, market concentration, or demand conditions
ree time dummies control time fixed effects. Exposure to the world market is covered
by the export rate.
6 res ults
We present our first-step results in the appendix. e conventional statistical tests for
fixed effects models are satisfactory. e fixed effects of all within-estimations are jointly
different from zero at high significance levels. Table 2 shows their distribution. For inter-
pretation purposes an artificial zero point is generated by subtracting the minimum (here:
-300,769). e firm-specific performance differential has a range of almost a million
euros per employee. is high range is to some extent due to the residual analysis. We
note especially the high overall range and the long tails of the distribution result from the
econometric construction of the fixed effects. When we compare only the 5
and 95
percentiles, the range shrinks to about €215,000. e interquartile range is about €66,800
per employee. ere are substantial differences in the productivity of establishments even
after we control for four types of input.
13 The industy classification is not taken from the Establishment Panel but from its extension the so called LIAB
( (2008-11-04)). The LIAB is the em-
ployer-employee panel of the IAB. However, we only use the industry information on establishment level. The
LIAB classification is more differentiated than the original establishment-panel variable. In both classifications
there are two structural breaks due to general overhauls of these classifications. We try to compensate for these
14 The industry dummies and the effects they control do not change very much over time. Thus, the dummies
would be eliminated by the within-estimator. These variables are sometimes described as quasi fixed, because
they can change over time but do so very rarely (e.g., Zwick (2004)). Hence, they should be included in the sec-
ond step. Given our data, we do not provide a detailed discussion of corporate parent and industry effects. A
recent account of this issue in the strategic management literature recommends “focussing toward the business
unit” (Misangyi et al. (2006, 587)), which we have done.
SBR 61 October 2009 393412 405
Table 2: Distribution of the establishment-specific performance differential
Percentile Centile 95% Conf. Interval With artificial
zero point
0 –300 769 –300 769 –300 769 0
5 –101 665 –115 767 –86 868 199 104
10 –69 677 –76 411 –63 491 231 092
15 –56 587 –61 646 –52 032 244 182
20 –44 049 –49 866 –37 575 256 720
25 –33 427 –37 441 –29 652 267 342
30 –25 407 –30 110 –22 435 275 362
35 –20 044 –22 801 –16 709 280 725
40 –14 028 –17 564 –10 786 286 741
45 –8 816 –11 678 –4 744 291 953
50 –2 713 –5 887 1 388 298 056
55 4 521 253 7 634 305 290
60 10 192 6 600 13 674 310 961
65 17 015 12 498 20 883 317 784
70 25 152 19 912 30 012 325 921
75 33 397 29 728 36 515 334 166
80 42 705 36 530 47 008 343 474
85 54 654 49 383 61 961 355 423
90 74 146 65 569 85 654 374 915
95 113 879 100 372 124 003 414 648
100 653 601 653 601 653 601 954 370
Obs.: 1092 Interquartile range 66 824
e second-step equation explains the variation of the firms’ specific productivity differ-
ential by their organizational characteristics. We use two different estimators.
e first estimator accounts for the problem of heteroskedasticity. e second specifica-
tion deals with the fact that the first-step estimation produces some extreme values for
the establishment specific effect. e heteroskedasticity-robust OLS estimator provides
corrected standard errors via a modified covariance matrix.
e outlier robust regression first fits the usual regression, then calculates Cook’s D and
excludes all observations with a D > 1 from further calculations. ereafter, we deter-
mine weights in an iterative procedure for which we use the absolute residuals. Finally,
we use these weights to estimate a weighted regression. is outlier-robust estimator is
SBR 61 October 2009 393412
especially well suited to deal with the long tails of the dependent variable’s distribution.
us, our interpretation rests mainly on those results, while the OLS estimator provides
a robustness check. Generally, the coefficients of both estimates have the same sign and a
similar magnitude. However, the significance levels vary. us, it seems plausible that at
least the direction of influence is stable.
Table 3: Results of the second step
OLS estimates with hetero-
skedasticity-robust standard errors
Coefficient t-value Coefficient t-value
Wage ratio 50 370*** 8.15 48 687*** 10.06
Works council 36 897*** 6.59 27 296*** 6.33
Empowerment 6 042 1.53 3 246 0.94
Team work –2 116 –0.60 –1 768 –0.56
Profit center 6 872* 2.03 7 644** 2.55
Quality control –2 163 –0.42 3 112 0.78
Outsourcing 1 947 0.62 2 692 0.94
Fluctuation ratio
Lag 0 52 0.02 –1 348 –0.76
Lag 1 –2 817*** –1.65 –2 885** –2.11
Lag 2 –3 890** –2.34 –3 043** –2.05
Fluctuation ratio squared
Lag 0 –143 –0.73 –38 –0.24
Lag 1 70 0.61 115 1.21
Lag 2 185** 2.28 178* 1.77
Information Technology 18 524*** 3.91 15 729*** 4.38
Export 315*** 4.17 351*** 5.81
Time dummies Three
Industry dummies 19
Constant –99 247*** –8.59 –101 225*** –12.1
Number of obs. 963 963
F-test F(37, 925) = 12.42*** F(37, 925) = 16.45***
Significance levels: * p < 0.1, ** p < 0.05, *** p < 0.01.
SBR 61 October 2009 393412 407
e positive, significant effect of the wage variable indicates that higher wages are accom-
panied by a higher productivity differential (Table 3 ). is finding is consistent with the
basic idea of efficiency wages. However, there are other explanations. For example, wages
usually rise with experience, but we are not able to control for this effect.
e productivity of establishments with works councils is €27,000 per employee higher
than those of establishments without works council. However, as indicated above, it is a
matter of debate whether a works council can be regarded as a practice or not.
Profit centers and investment in information and communication technology have a posi-
tive, significant influence on the establishment-specific performance differential. Empower-
ment and outsourcing have positive but nonsignificant effects. All these practices appear
to contribute to organizational capital.
e coefficient pattern for the involuntary quit rate is more complex. For the first and
second lags, the linear variable has significant negative coefficients. us, a higher quit rate
leads to less value added. Self-binding rules appear to generate economic value. However,
the second lag of the squared value of the layoff ratio has a positive and (weakly) signifi-
cant sign. us, in some instances, layoffs improve performance. is finding underlines
an important point: whether or not a specific practice is generating organizational capital
depends to a certain degree on the circumstances15.
In Table 4 we estimate the economic value of practices that enhance organizational capital.
We do so by inserting the variable values for each firm into the estimated function. We
omit variables with nonsignificant coefficients and control variables, because they do not
contribute to organizational capital.
For a robustness check we also estimate the part of the performance differential that is
explained by all practices, including the nonsignificant coefficients. e difference between
the two approaches is small. We use the coefficient of the zero lag fluctuation ratio for
the estimates even though its coefficient is nonsignificant. We believe that in this case, it
makes more sense to use the whole set to reflect the time structure of the fluctuation vari-
able. However, the squared values are only control variables and thus they are not part of
the estimates provided in Table 4, regardless of their significance level.
15 Similar results were found by Schneider (2008).
SBR 61 October 2009 393412
Table 4: Estimated contribution of organizational practices to the establishment-
specific performance differentials
Percentile Centile 95% Conf. Interval Artifical zero point
0 –1 191 –1 191 –1 191 0
5 42 543 38 781 46 177 43 734
10 56 896 51 350 59 429 58 087
15 63 795 60 450 67 018 64 986
20 70 410 67 182 73 396 71 601
25 75 647 72 977 77 823 76 838
30 79 913 77 361 82 371 81 104
35 84 010 81 786 86 229 85 201
40 87 456 85 411 89 315 88 647
45 90 242 88 469 91 741 91 433
50 92 687 91 010 94 159 93 878
55 94 980 93 563 96 161 96 171
60 96 747 95 629 98 256 97 938
65 98 728 97 766 100 319 99 919
70 100 829 100 025 102 164 102 020
75 103 274 101 870 104 418 104 465
80 105 683 104 096 107 281 106 874
85 109 738 107 407 111 611 110 929
90 114 520 112 231 117 704 115 711
95 123 981 121 317 126 499 125 172
100 156 450 156 450 156 450 157 641
Obs.: 936 Interquantile range: 27 627
Table 4 gives the distribution of the resulting estimates and the artificial zero point. e
portion of the range of the firm-specific performance differential that can be explained
by the practices constituting organizational capital, including the works council variable,
is about €157,600 per employee. e interquartile range is €27,600 per employee. is
value is considerable. In our data set the average gross wage sum per employee is about
€26,400, and the average added value is €60,000.
7 COn Cl us i On
n this paper we discuss the theoretical concept of organizational capital and empirically iden-
tify its productive impact and its value. We define organizational capital as sets of organiza-
tional practices, processes, and designs that make it possible for companies to extract a higher
level of returns from a given resource endowment. Such organizational capital is intangible,
not tradable, and idiosyncratic. Due to these characteristics, it is hard
to measure.
SBR 61 October 2009 393412 409
We measure organizational capital, or, more precisely, its impact on establishment
performance, by using establishment level data and fixed effects models in a two-step
procedure. Retrieving the fixed effects in the first step provides establishment-specific
performance differentials. ese differentials are quite large. In our view, some portion
of these differentials is due to the different and mostly idiosyncratic ways to organize
the production.
To determine the share of the performance differential that is attributable to organiza-
tional practices, we regress the variation of the fixed effects on organizational practices. If
these practices contribute significantly to the idiosyncratic performance differential, then
they contribute to organizational capital. Such practices include wage premia, self-binding
rules, profit centers, and IT - investments. Using the estimates for the contribution of
these practices, we derive the share of the performance differential that can be attributed
to their use. We find that this share is substantial. In other words, organizational capital
can generate substantial value.
app en d ix
Table 5: Results of the relevant first step estimates
1997-1999 1999-2001 2000-2002 2003-2005
Number of obs. 571 670 869 1210
Number of groups/
Obs. per group 278
min: 1
avg: 2.1
max: 3
min: 1
avg: 2
max: 3
min: 1
avg: 1.8
max: 3
min: 1
avg: 2.3
max: 3
F-test F(8, 285) = 8.59 F(8, 327) = 2.27 F(8, 372) = 3.29 F(8, 665) = 5.34
Prob > F: 0.000 Prob > F: 0.022 Prob > F: 0.001 Prob > F: 0.000
R20.19 0.05 0.066 0.060
Coefficient t-value Coefficient t-value Coefficient t-value Coefficient t-value
lnEmployment 1.113 7.10 0.800 3.54 0.678 3.76 0.588 4.13
Skilled ratio –0.086 –1.97 –0.018 –0.62 –0.016 –0.59 0.037 1.75
lnCapital 0.119 3.18 –0.024 –1.37 –0.029 –2.25 0.024 2.06
Fluctuation ratio
Lag 1 –0.019 –0.96 0.015 0.70 0.040 1.69 0.018 1.87
Lag 2 –0.010 –0.50 –0.012 –0.62 –0.009 –0.37 0.016 1.47
Share of part time 0.002 0.47 –0.008 –1.50 –0.003 –0.46 –0.009 –2.86
Constant 8.681 8.33 12.630 9.95 13.223 13.08 12.920 17.00
SBR 61 October 2009 393412
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... Ludewig and Sadowski (2009) empirically examine the economic value of organizational capital. They use a comprehensive panel data set from the Institute for Employment Research (IAB) that provides standard information about inputs and outputs of the production process of German corporate establishments. ...
... Moreover, we can determine if the management delegated decision-making power to line workers and whether supply by external vendors increased or outsourcing took place. Using these organizational practices as measures for organizational capital and a sophisticated econometric methodology, Ludewig and Sadowski (2009) find that except for profit centers, none of the measures for organizational capital exerts a significant impact on the performance of the establishments. The paper advances our knowledge on the value of organizational capital by shedding light on what particular practices contribute to organizational capital. ...
... For example, two specific practices might be linked by a complementary relationship in the sense of Milgrom and Roberts (1995). In the specification used by Ludewig and Sadowski (2009), ignoring complementarities leads to an omitted variable bias. Furthermore, measuring performance is a critical issue. ...
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Ludewig and Sadowski (2009) empirically examine the economic value of organizational capital. They use a comprehensive panel data set from the Institute for Employment Research (IAB) that provides standard information about inputs and outputs of the production process of German corporate establishments. This data set also includes organizational dimensions of those establishments, which makes it an interesting source for a study on organizational capital.
... These conditions are related mostly to the intangible resources (human and social capital) as the highest valued organisational units today [27]. Only the part of organisational capital that cannot be imitated, social and human capital, can generate a sustainable competitive advantage, and therefore represent an invaluable organisational component. ...
... Only the part of organisational capital that cannot be imitated, social and human capital, can generate a sustainable competitive advantage, and therefore represent an invaluable organisational component. Therefore, to define organizational capital we must concern its effects on all performance measures [27]. Therefore, the special focus of scholars towards this concept is reasonable and justified. ...
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This work proposes a task-based methodology for the measurement of employment and investment in organisational capital (OC) in 20 OECD countries. It builds on the methodology of Squicciarini and Le Mouel (2012) and uses information from the OECD Programme for the International Assessment of Adult Competencies (PIAAC). OC is defined as firm-specific organisational knowledge resulting from the performance of tasks affecting the long-term functioning of firms, such as developing objectives and strategies; organising, planning and supervising production; and managing human resources. Cross-country heterogeneity in OC-related occupations emerges: while 20 occupational classes of the International Standard Classification of Occupations (ISCO 2008) are on average identified as being OC-related, country-specific values range between 14 (in Korea) and 24 occupations (in Poland). A core group of managerial occupations are consistently identified as OC occupations across countries, whereas differences arise in the selection of professionals and associate professionals in science and engineering, health, education, and business administration. Estimates suggest the share of OC occupations in total employment to amount to 16% on average, with country-specific values that vary between 9.5% (Denmark) and 26% (United Kingdom); and that total investment in OC, as a share of value-added, ranges from 1.4% in the Czech Republic to 3.7% in the United Kingdom, with an average 2.2% across all countries. Managers appear to account for less than half of total employment and investment in OC. Total investment in OC results higher in services than in manufacturing. In the services sector, on average half of investment in OC comes from small firms, while in manufacturing, 45% of investment in OC comes from large firms. Finally, the importance of OC investment in the public sector is investigated. With only few exceptions, investment in OC is higher in the public sector than in the private sector. These estimates of OC investment can be used to analyse its role with respect to skill use and mismatch, its impact on the routinisation of tasks and resulting polarisation of wage distribution, and its role in firms' integration and upgrading along global value chains (GVC).
Purpose – The purpose of this paper is to identify a measure of intellectual capital (IC) value which offers new research opportunities for empirical investigations and to examine the determinants of IC value. Design/methodology/approach – In total, 4,488 firm years of German companies are investigated to compare three measures of IC value: market-to-book, Tobin’s q, and long-run value-to-book (LRVTB). Findings – LRVTB is observed to be the IC value measure with the highest explanatory value. This measure provides an approach to empirically test previously untested hypotheses on IC value. The results on testing determinants of IC value indicate that IC value is positively related to leverage and motivational payments to employees and negatively associated with company size. In contrast, recognised intangible assets, research and development (R&D), company age and concentrated ownership show no significant effects. Research limitations/implications – The findings on IC value measures contribute to IC research as they offer a way to estimate IC value for testing IC-related hypotheses. The findings on IC determinants have implications for IC management as the relevant determinants can be considered for IC value creation. Originality/value – This paper responds to the challenge posed by previous IC research to develop more creative quantitative approaches to estimate IC value (Marr et al., 2003; Mouritsen, 2006) in order to test IC-related hypotheses by innovatively applying a measure from mergers and acquisitions research to IC.
This paper develops a two-sector dynamic stochastic general equilibrium model to measure intangible capital stock and studies the implied riskiness of market value of capital. The equilibrium of the economy is characterized by a state-space representation of dynamic system. Kalman filter algorithm is used to produce an estimate of the value of intangible capital stock based on the observed data on macroeconomic variables and asset prices. With modest capital adjustment cost, the model implies that significant amount of intangible capital is accumulated during past 50 years in US economy but the growth of intangible capital in the last decade is not as fast as the estimates of Hall (2001). Variation in intangible capital estimated from aggregate macroeconomic variables, accounts for almost half of the variability in the market-to-book ratio of non-financial and non-farm corporate firms.
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Employees are motivated intrinsically as well as extrinsically. Intrinsic motivation is crucial when tacit knowledge in and between teams must be transferred. Organizational forms enable different kinds of motivation and have different capacities to generate and transfer tacit knowledge. Since knowledge generation and transfer are essential for a firm's sustainable competitive advantage, we ask specifically what kinds of motivation are needed to generate and transfer tacit knowledge, as opposed to explicit knowledge.
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We evaluated the impact of human resource (HR) managers' capabili- ties on HR management effectiveness and the latter's impact on corpo- rate financial performance. For 293 U.S. firms, effectiveness was asso- ciated with capabilities and attributes of HR staff. We also found rela- tionships between HR management effectiveness and productivity, cash flow, and market value. Findings were consistent across market and accounting measures of performance and with corrections for biases.
Zusammenfassung Auf der Basis eines zusammengefügten Datensatzes aus dem IAB-Betriebspanel und der Historikdatei der Beschäftigtenstatistik wurde für 1995 für das westdeutsche Produzierende Gewerbe ein Translog-Kostensystem für sechs Qualifikationsgruppen (Arbeiter und Angestellte jeweils in un-/angelernte, qualifizierte und hochqualifizierte Beschäftigte unterteilt) geschätzt. Untersucht wurden die aus der betrieblichen Kostenfunktion für unterschiedlich qualifizierte Qualifikationsgruppen sich ergebenden Substitutionsmöglichkeiten. Die ermittelten Substitutionsbeziehungen innerhalb der einzelnen Arbeitergruppen sind denen innerhalb der einzelnen Angestelltengruppen sehr ähnlich: Qualifizierte - und zu einem geringeren Maße auch Hochqualifizierte - erweisen sich als Substitute für Un-/Angelernte. Dies könnte zumindest teilweise den Anstieg der Arbeitslosigskeit der Un- und Angelernten erklären. Demgegenüber werden Qualifizierte und Hochqualifizierte vom Lohn der jeweils anderen Gruppe nicht beeinflußt. Eine mit der Qualifikation abnehmende Eigenlohnelastizität zeigt sich zwischen Qualifizierten und Hochqualifizierten, nicht jedoch zwischen Un-/Angelernten und Qualifizierten. Zwischen Arbeitern und Angestellten sind die Substitutionsbeziehungen relativ gering, wobei un-/angelernte, qualifizierte und hochqualifizierte Arbeiter jeweils zur analogen Angestelltengruppe in komplementärer Beziehung stehen. Schließlich kann die These einer stärkeren Komplementarität zwischen qualifizierten Arbeitskräften und Sachkapital als zwischen nicht formal qualifizierten Arbeitskräften und Sachkapital nicht bestätigt werden.
This chapter describes a firm-specific measure of organization capital and applies it to produce estimate for a large sample of publicly traded companies. It explains that this measure involves the measure organizational capital as a residual, much like total factor productivity. This chapter also evaluates the validity of this measure within a widely used investment valuation model and shows that it can contribute significantly to the explanation of differences in market values of firms, beyond the traditional value indicators of assets in place and expected abnormal earnings.