- Original article
- Open Access
- Published:

# Once an entrepreneur, always an entrepreneur? The impacts of skills developed before, during and after college on firm start-ups

*IZA Journal of Labor Economics*
**volume 4**, Article number: 9 (2015)

## Abstract

By allowing agents to switch from entrepreneurship to wage work and vice versa over the life cycle, this study proposes a dynamic Jacks-of-All-Trades (JAT) model where entrepreneurs invest in highly varied skills to manage their business. We simultaneously endogenize human capital investment and occupational decisions. Using the survey data of Iowa State alumni graduating between 1982 and 2006, we find that the probability of selecting a broad curriculum, having a more varied career, and becoming an entrepreneur are jointly positively correlated. Academic diversity is found to be initially important in starting a business shortly after completing schooling, but its importance declines over time.

At the heart of economic growth theories is the need for entrepreneurs to make profitable investments in capital, research and development, or technological advancements. In making investments that profit themselves, entrepreneurs also profit the rest of the economy. The key mechanism is an underlying complementarity between the entrepreneur and the inputs they employ. Rosen (1983); Schultz 1988; and Murphy, Schleifer and Vishny (1991) argued that the complementarities between entrepreneurial skills and other workers create returns to scale in managerial abilities. Indeed, the spillovers from the entrepreneur’s skill or knowledge to that of others in society are a common mechanism generating endogenous growth (Romer 1986, 1990; Lucas and Robert 2002). McMillan and Woodruff (2002) found that the most successful transition economies were the ones that fostered the entrepreneurial skills necessary to allocate resources efficiently in the face of the tremendous economic shocks buffeting those countries.

As argued by Iyigun and Owen (Iyigun and Owen 1998), there is an increasing incentive to apply rare managerial skills to the more secure returns offered by professional occupations as economies develop. Therefore, as economies are exposed to more rapid changes in technologies, competitive pressures and price shocks, it becomes increasingly important to identify and develop the policies and skills that lead to successful entrepreneurial entry. Past empirical work has tied entrepreneurship to whether parents owned a business (Dunn and Holtz-Eakin, 2000; Fairlie and Robb, 2007; Jia and Lan, 2013; Lechmann and Schnabel 2014); ethnicity (Borjas and Bronars, 1989; Fairlie and Meyer, 2000; Fairlie, 1999); access to finance (Holtz_Eakin et al., Holtz-Eakin et al. 1994; Dunn and Holtz-Eakin, 2000); managerial attributes (Fairlie, 2002); government tax and transfer policies (Blau 1987); technical change lowering minimum efficient scale (Blau 1987); and business cycle conditions (Evans and Leighton, 1989). However, not until Lazear’s (2004, 2005) work did empirical tests directly confront the unobserved entrepreneurial ability that drives the models of Rosen, Schultz, Murphy et al., Romer and Lucas.

Lazear (2004, 2005) hypothesized that entrepreneurs have an innate managerial skill that drives their interest to enter entrepreneurship. However, to be successful, entrepreneurs need to be able to understand and direct many aspects of their operations. That requires a diversity of skills that can complement the more specialized skills of their employees. Entrepreneurs will invest in a broad range of skills that insure at least a minimum competency in all the areas that are critical to the functioning of their business. Consequently, entrepreneurs become “Jacks-of-All-Trades” (JAT). In contrast, their employees are rewarded for their maximum production capacities. That means laborers have an incentive to specialize their human capital investments in a single area so as to hone a single skill to its maximum potential. Lazear used data on the educational and occupational choices made by a sample of Stanford MBA graduates to test the model’s predictions. He measured the breadth of skills alternatively by the number of professional positions held or by the breadth of the academic program in business school. More specialized students chose to work for others, while more generally trained students were more likely to start a business after graduation.

Several studies have tested the predictions of the JAT theory. Wagner (2006) and Lechmann and Schnabel (2014) found more general skills led to a higher probability of entrepreneurship. However, alternative interpretations of the link between general human capital investments and entrepreneurship have been advanced. Åstebro and Thompson (2011) and Oberschachtsiek (2009) examined whether the correlation between breadth of human capital investments and entrepreneurship was due instead to a taste for variety. They hypothesized that individuals with greater tastes for variety may seek out more varied careers including entrepreneurial ventures, finding mixed evidence on whether the taste for variety or JAT was more consistent with the data. In a similar vein, Silva (2007) argues that unobservable taste or productive factors lead to both greater breadth of human capital investments and entrepreneurship in Italy. He finds that after controlling for individual fixed effects, the significant positive correlation between past number of jobs and probability of entering entrepreneurship disappears. However, his methodology does not rule out that both entrepreneurial entry and occupational choices are due to an innate unobserved ability, the ultimate driver in the Lazear model. A recent study by Hsieh, Parker and Praag (2011) further finds that more risk averse individuals are more likely to invest in balanced skill profiles and therefore are likely to become entrepreneurs, using the Dutch university graduates dataset. Even within workplaces, workforce educational diversity within a firm in Denmark is found to promote entrepreneurial behavior of employees as well as the formation of new firms (Marino et al. 2012).

This study’s contribution to the empirical and theoretical work on the "Jack-of-all-Trades" model is to build in the timing of the human capital and occupational choices more explicitly. In doing so, we can examine the variety of educational experiences, variety of working experiences, and entrepreneurial entry as joint decisions. We evaluate those decisions at different times in the life cycle: after leaving high school; after leaving college; and after a period of time in the labor force. In doing so, we can examine the theoretical and empirical implications of allowing individuals to enter or leave entrepreneurship as they learn about their entrepreneurial abilities over time. Our analysis uses a unique data set of more than 5,000 survey responses from Iowa State University (ISU) alumni graduating with a Bachelor’s degree between 1982 and 2006. The survey, conducted by the end of 2007, includes questions about business start-ups, work histories of alumni after graduation, and family background, socioeconomic characteristics and extra-curricular activities before college. Information on academic diversity and success was merged in using data from each student’s academic record in the University.

Consistent with our logical extensions of the JAT, we find that unobservable productivities for entrepreneurship have common positive effects on breadth of college curriculum, diversity of occupational experiences, and probability of starting a business. Students with more diverse academic programs are more likely to enter entrepreneurship. As time since graduation increases, the importance of academic diversity declines, while the diversity of work experiences since college becomes more important. In particular, we find that individuals whose academic programs are more specialized may ultimately enter entrepreneurship, but are more likely to do so by picking more diverse occupational experiences to broaden their human capital portfolios before starting a business.

The next section extends Lazear’s "Jack-of-all-Trades" model of entrepreneurship to two periods to show how and why occupational decisions can change over the life cycle, driven by both the mechanism of JAT theory and the unobserved entrepreneurial abilities. The theory leads to an empirical strategy which we outline next. Then, we present a summary of the data used to evaluate academic, occupational and entrepreneurial decisions. Section 4 proposes an empirical strategy and test hypotheses and reviews the empirical results. The last section concludes the paper.

## 1 A model of occupational, educational, and entrepreneurial choices

We illustrate the key elements of the entrepreneurial entry decision using a two-period model of human capital choices and occupational choices^{1}. At the start of the first period, individuals encounter an entrepreneurial shock and simultaneously choose whether to be an entrepreneur or a laborer based on their expected entrepreneurial abilities. The choice of occupation is made simultaneously with human capital investments so as to maximize expected lifetime earnings. Then at the beginning of the second period, individuals may adjust their career and human capital choices upon receiving updated information on their true entrepreneurial abilities. Individuals who switch occupations will have to modify their human capital investments and may end up with some skills that are no longer used in period 2.

Following Lazear (2005), we assume that a laborer’s income is related to specialized skills. Thus, if human capital is measured along two dimensions, \( {x}_1^t \) and \( {x}_2^t \) in period *t*, the payoff function for a laborer in period *t* is associated with the skill that represents his comparative advantage, \( {Y}_L^t= \max \left({x}_1^t,{x}_2^t\right),\ t=1,\ 2 \). On the other hand, entrepreneurs are "jacks-of-all-trades" whose payoff depends on holdings of both skills. If the generation of entrepreneurial earnings is subject to a Leontief technology in the two skills, entrepreneurial earnings are given by \( {Y}_E^t={\lambda}_t min\left({x}_1^t,{x}_2^t\right), \) where entrepreneurial skill *λ*
_{
t
} > 1.^{2} This entrepreneurial skill evolves over time such that *λ*
_{
t
} = *λ*
_{
t − 1} + *ε*
_{
t
}, where *ε*
_{
t
} is governed by a white noise process. *λ*
_{
t
} and *λ*
_{
t − 1} are positively correlated, indicating that entrepreneurial learning takes place over the life cycle. At the start of each period, the individual learns *ε*
_{
t
}, and so *λ*
_{
t
} becomes fully observed. As *λ*
_{
t
} increases, entrepreneurial earnings rise relative to being a laborer, and so the probability of choosing entrepreneurship increases. That means that *λ*
_{
t
} will have a reservation property such that only individuals with *λ*
_{
t
} ≥ *λ** will become entrepreneurs.

To make this precise, let the level of skill selected in period *t* be

\( {H}_t={x}_1^t+{x}_2^t,\ t=1,\ 2, \) where *H*
_{
t
} is exogenously given. Individual’s strategy is choosing an optimal combination of \( {x}_1^t \) and \( {x}_2^t \) so as to maximize income. Specifically, at the start of period 1, each individual chooses whether to be an entrepreneur (*E*
_{
1
}) or a laborer (*L*
_{
1
}) and chooses to invest in appropriate skill levels \( {x}_1^t \) and \( {x}_2^t \). We assume individuals are risk neutral, and so the choices are made so as to maximize lifetime income^{3}:

where \( {Y}^1= Max\left\{{\lambda}_1 min\left({x}_1^1,{x}_2^1\right), max\left({x}_1^1,{x}_2^1\right)\right\} \) and

Individuals who receive a draw on entrepreneurial skill *λ*
_{
1
}
*≥ 2* will become entrepreneurs in the first period^{4}. In doing so, they would invest in skills such that \( {\widehat{x}}_1^1={\widehat{x}}_2^1=\frac{H_1}{2} \) with expected earnings equal to \( {Y}^1={\lambda}_1{\widehat{x}}_1^1={\lambda}_1{\widehat{x}}_2^1 \). Because the expected entrepreneurial skill in period 2 will be *E*(λ_{2}) = λ_{1}, entrepreneurs will expect to set \( {\widehat{x}}_1^2={\widehat{x}}_2^2=\frac{H_2}{2} \) in period 2 and earn \( \mathrm{E}\left({Y}^2\right)={\uplambda}_1\left({\widehat{x}}_1^1+{\widehat{x}}_1^2\right) = {\uplambda}_1\left({\widehat{x}}_2^1+{\widehat{x}}_2^2\right)=\frac{H_1+{H}_2}{2} \).

Individuals with weak draws on λ_{1} in period 1 such that λ_{1} < 2 will become laborers. They will want to specialize in producing only \( {x}_1^1 \) or only \( {x}_2^1 \) because they can only extract a reward from one of the two skills. Laborer earnings will be either \( {Y}^1={\widehat{x}}_1^1={H}_1 \) or \( {Y}^1={\widehat{x}}_2^1={H}_1 \). The best forecast a laborer can make of his next draw on entrepreneurial skill in period 2 will be *E*(λ_{2}) = λ_{1} < 2, and so he will expect to be a laborer in period 2 as well, continuing to invest in the same skill in period 2 that he specialized in during period 1. If the laborer specialized in skill \( {\widehat{x}}_j^1 \) in period 1, his expected earnings in period 2 will be \( E\left({\mathrm{Y}}^2\right)={\widehat{x}}_j^1+{\widehat{x}}_j^2={H}_1+{H}_2 \).

Everyone enters period 2 with the optimal skill portfolio \( \left({\widehat{x}}_1^1,{\widehat{x}}_2^1\right) \) from period 1 and the occupation decisions {*E*
_{1}, *L*
_{1}}. They also learn their true *λ*
_{
2
}
*= λ*
_{
1
}
*+ ε*
_{
2
}. At that point, each individual can reassess whether to stay with their planned occupation and projected skill decisions or to change. The occupational choice at the beginning of the second period is

This leads to four possible cases:

*Case 1* An individual is an entrepreneur in both periods 1 and 2.

*Case 2* An individual is an entrepreneur in period 1 but becomes a laborer in period 2.

*Case 3* An individual is a laborer in period 1 but switches to become an entrepreneur in period 2.

*Case 4* An individual is a laborer in both periods 1 and 2.

We will discuss each of these cases in turn, using Figure 1 to illustrate the conditions that would cause someone to switch occupations. It should be apparent that if entrepreneurial abilities were known with certainty so that ε_{2} = 0, individuals would never switch. Therefore, learning one’s potential for opening or managing a business occurs gradually over time. Figure 1 illustrates the conditions for entrepreneurial entry and persistence as a function of initial information on entrepreneurial ability (*λ*
_{
1
}) and acquired information (*λ*
_{
2
}).

### Case 1: Persisting entrepreneurs

For an individual to be an entrepreneur in period 1, *λ*
_{
1
}
*≥ 2* and \( {\widehat{x}}_1^1={\widehat{x}}_2^1=\frac{H_1}{2} \). These are individuals who locate beyond *λ*
_{1} = 2 in quadrant I of Figure 1. To remain an entrepreneur in period 2, \( {\lambda}_2\ge 1+\frac{H_2}{H_1+{H}_2}<2 \) in quadrant II, and so there is a tendency to persist as an entrepreneur in period 2, even with a negative draw on ε_{2}. The individuals for whom \( 1+\frac{H_2}{H_1+{H}_2}<{\lambda}_2<2 \) would have chosen to be laborers in period 1 if they had perfect knowledge of their entrepreneurial abilities in period 1 (i.e., if they knew ε_{2}). They remain entrepreneurs because their human capital investments in period 1 are irreversible and they cannot acquire enough specialized human capital in period 2 to make a transfer to laborer financially attractive.^{5} Individuals are more likely to persist as entrepreneurs when avenues for additional human capital accumulations in period 2 are limited relative to period 1 (*H*
_{2} ≪ *H*
_{1}) as well as when they experience positive realizations on ε_{2}. Earnings for persisting entrepreneurs will be \( {Y}^2={\lambda}_2\left(\frac{H_1+{H}_2}{2}\right), \) and so the range of earnings for persisting entrepreneurs is indicated by the upward sloping line *Y*
_{
2
} that begins at point A in quadrant II*.*

### Case 2: exiting entrepreneurs

An individual who initially enters entrepreneurship and then switches to laborer status will devote skill investment in period 2 into only one of the two options, \( {x}_1^2 \) or \( {x}_2^2 \). Abandoning entrepreneurship will be optimal if \( {\lambda}_2<1+\frac{H_2}{H_1+{H}_2} \), and so these individuals locate to the right of \( \frac{H_1 + 2{H}_2}{H_1+{H}_2} \) in quadrant II. In switching to laborer status, former entrepreneurs will get no reward from half their period 1 human capital investment, and so their period 2 earnings will be \( {Y}_2=\frac{H_1}{2}+{H}_2 \). Exiting entrepreneurs are the ones who experience large negative realizations of ε_{2}, meaning that they made a big mistake in assessing their entrepreneurial skill in period 1. There will be more entrepreneurs exiting to laborer status if there are substantial opportunities to acquire specialized skills in period 2 relative to period 1 so that *H*
_{2} ≫ *H*
_{1}.

### Case 3: exiting laborers

An individual who is a laborer in period 1 devotes *H*
_{1} entirely to one skill, either \( {x}_1^1 \) or \( {x}_2^1 \) and earns *Y*
_{1} = *H*
_{1}. For that person to switch to entrepreneurship, he would have to invest intensively in the other skill in period 2 so that by the end of period 2, \( {\widehat{x}}_1^1+{x}_1^2 \) is as close to \( {\widehat{x}}_2^1+{x}_2^2 \) as possible. How close he can get depends on the relative opportunities for human capital acquisition in period 2 versus period 1.

### Case (3.A) *H*
_{2}
**≥**
*H*
_{1}

*H*

*H*

Without loss of generality, suppose that all of the period 1 skill investment was in \( {\widehat{x}}_1^1 \). When there is greater opportunity to add human capital in period 2, all of period 2 investment would be in \( {x}_2^2 \) up to the point where \( {\widehat{x}}_1^1={x}_2^2 \). From then on, the entrepreneurial entrant would devote equal time to the two skills. Accumulated human capital would be \( \frac{H_1+{H}_2}{2} \). That switch from laborer to entrepreneur would only make sense if \( {Y}_2={\lambda}_2\left(\frac{H_1+{H}_2}{2}\right) \)
*> H*
_{1} + *H*
_{2} or *λ*
_{2} > 2. This condition does not depend on human capital accumulations, and so switching into entrepreneurship in Case (3.A) will depend only on the size of *ε*
_{2}. Because of the higher ability to invest in human capital in period 2, these entrepreneurs will have the same human capital as if they had devoted period 1 to entrepreneurship as well.

The range of earnings for persisting entrepreneurs is indicated by the upward sloping line *Y*
_{
2
} that begins at point B in quadrant II*.* Consequently, the range of earnings for those who switch into entrepreneurship in period 2 excludes the lower tail of earnings for persisting entrepreneurs.

### Case (3.B) *H*
_{2} < *H*
_{1}

*H*

*H*

Again, assume that all of the period 1 skill investment was in \( {\widehat{x}}_1^1 \). When opportunities to invest in additional human capital are more limited in period 2 than period 1, all of period 2 investment would be in \( {x}_2^2={H}_2<{H}_1={\widehat{x}}_1^1 \). Entrepreneurial income will be set by H_{2}, and so some of the period 1 investment in \( {\widehat{x}}_1^1 \), namely (*H*
_{1} − *H*
_{2}), will be wasted. Laborers will switch to entrepreneurship only if \( {Y}_2^{\hbox{'}}={\lambda}_2{H}_2>{H}_1+{H}_2 \)
*or*
\( {\lambda}_2>1+\frac{H_1}{H_2}>2 \). Therefore, the condition for switching from laborer to entrepreneur requires an even larger positive shock \( {\varepsilon}_2>\frac{H_1}{H_2}-1 \) than was required in Case (3.A). Note that if human capital investments are subject to diminishing marginal products, Case (3.B) is more plausible than is Case (3.A).

The range of earnings for exiting laborers governed by Case (3.B) is given by the upward sloping line \( {Y}_2^{\hbox{'}} \) that begins at point C in quadrant II. These entrepreneurs will earn less than persisting entrepreneurs with identical entrepreneurial skills *λ*
_{
2
} because of the wasted human capital from period 1.

### Case 4: persisting laborers

An individual who becomes a laborer in period 1 will remain a laborer in period 2 if *λ*
_{2} < 2. It is optimal to continue specializing in the same skill selected in period 1, and so if \( {\widehat{x}}_j^1>0 \), then \( {x}_j^2>0 \) for continuing laborers. Period 2 earnings for continuing laborers will be *Y*
_{2} = *H*
_{1} + *H*
_{2} as shown in quadrant II of Figure 1
*.*

## 2 Probability of becoming an entrepreneur

Let *q* be the probability of becoming an entrepreneur at any point in life. Based on our formulations in Cases 1 and 3,

Then we will have

\( q={\displaystyle {\int}_2^{\infty }}d{\uplambda}_1{\displaystyle {\int}_{1+\frac{H_2}{H_1+{H}_2}-{\uplambda}_1}^{\infty }}g\left({\uplambda}_1,{\upvarepsilon}_2\right)d{\upvarepsilon}_2+{\displaystyle {\int}_1^2}d{\uplambda}_1{\displaystyle {\int}_{2-{\uplambda}_1}^{\infty }}g\left({\uplambda}_1,{\upvarepsilon}_2\right)d{\upvarepsilon}_2 \) when *H*
_{2} ≥ *H*
_{1}

and

\( q={\displaystyle {\int}_2^{\infty }}d{\uplambda}_1{\displaystyle {\int}_{1+\frac{H_2}{H_1+{H}_2}-{\uplambda}_1}^{\infty }}g\left({\uplambda}_1,{\upvarepsilon}_2\right)d{\upvarepsilon}_2+{\displaystyle {\int}_1^2}d{\uplambda}_1{\displaystyle {\int}_{1+\frac{H_1}{H_2}-{\uplambda}_1}^{\infty }}g\left({\uplambda}_1,{\upvarepsilon}_2\right)d{\upvarepsilon}_2 \) when *H*
_{2} < *H*
_{1}.

It can be shown that \( \frac{\partial q}{\partial \left(\frac{H_1}{H_2}\right)}>0 \) when *H*
_{
2
}
*≥ H*
_{
1
}
^{6}
*.* A marginal increase in the relative importance of *H*
_{1} over *H*
_{2} will lead to a higher tendency to start a business. We therefore expect that skill diversity in the first period will affect entrepreneurship to a larger degree as \( \frac{H_1}{H_2} \) increases. In our empirical work, we will presume that *H*
_{
2
} rises relative to *H*
_{
1
} as the length of period 2 increases.

### Empirical strategy

Cases 1 and 4 are the ones that were derived in Lazear (2005). Our extension to a second period leads to Cases 2 and 3A-B in which individuals can change their entrepreneurial choices over the life cycle. These four cases allow us to derive several predictions that we can take to the data. For our purposes, it is useful to frame these predictions in the context of when we observe individual behavior, at the start of period 1 or at the start of period 2.

#### Period 1

During period 1, individuals will be planning their human capital investments, given their expected entrepreneurial skill λ_{1}. Because λ_{1} is unobservable to the econometrician, it will be a source of error in equations explaining the endogenous choices of human capital and occupation.

Let \( Var\Big({H}_{1i}^s \)
*)* be the variance in the schooling investments pursued by individual *i*. A highly varied education portfolio would include broad training over many different fields. A low variance education portfolio would involve many credits in a single major with limited exposure to coursework outside the major. Following Lazear’s (2005) terms, high variance academic programs are pursued by generalists, and low variance programs are pursued by specialists. Similarly, let \( Var\Big({H}_{1i}^o \)) be the variance in the types of occupational or industrial human capital pursued by individual *i*. Generalists would pick highly varied occupational experiences or wide ranging sectors of the economy, while specialists would focus on a narrow range of job experiences. The choice to enter entrepreneurship *E*
_{
i
} will be made more profitable with the high levels of \( Var\left({H}_{1i}^s\right) \) and \( Var\left({H}_{1i}^o\right) \)
*.* If *Z*
_{
i
} is a vector of individual attributes known at the start of period 1 that affects relative earnings in entrepreneurial versus laborer occupations, we can characterize the choices available to individual *i* at the start of period 1 as

where the right-hand-side of the last equation is the reduced form representation of the structured relationship between *E*
_{
i
} and \( Var\left({H}_{1i}^S\right) \)
*,*
\( Var\left({H}_{1i}^O\right) \) and *Z*
_{
i
}. We assume that the error terms \( {\xi}_{1i}^E \)
*; k* = *S*, *O*, *E*
_{1} are identically and independently distributed such that \( Cov\left({\xi}_{1i}^k,{\xi}_{1i}^l\right) \)
*=0*. However, the compound errors \( {v}_{1i}^k={\beta}_Z^k{\lambda}_{1i}+{\xi}_{1i}^k \)
*; k* = *S*, *O*, *E*
_{1} will be correlated because of the common unobserved entrepreneurial skill.

#### Proposition 1.1 \( Cov\left({v}_{1i}^k,{v}_{1i}^l\right)>0;k\ne l. \)

Because high values of *λ*
_{1} lead to broader human capital investments, we would expect \( {\beta}_{\lambda}^k>0 \)
*, k* = *S*, *O*, *E*
_{1}. Therefore, the theory requires that \( Cov\left({v}_{1i}^k,{v}_{1i}^l\right)>0. \)

#### Proposition 1.2 \( sgn\left({\beta}_Z^k\right)=sgn\left({\beta}_Z^l\right);k\ne l. \)

The maintained hypothesis underlying the theory is that human capital investment and entrepreneurial choices are being made simultaneously so as to increase expected lifetime earnings. Consequently, if *Z*
_{
i
} raises expected entrepreneurial income and increases the probability that *E*
_{1i
}
*= 1*, then it will also increase \( Var\left({H}_{1i}^S\right) \) and \( Var\left({H}_{1i}^O\right) \).

#### Start of Period 2

At the start of period 2, the individual receives the draw on *λ*
_{
2
}. Because the innovation *ε*
_{2} is white noise and *Cov*(*λ*
_{1}, *λ*
_{2}) > 0, there will be persistence in the entrepreneurial and human capital choices undertaken in period 1. However some individuals will receive sufficiently large positive or negative draws on *ε*
_{2}, which induces a change into or out of entrepreneurship. As a result, there will be several other predictions that can be derived from the theory.

We define period 2 empirically as the period following completion of formal schooling. By that time, individuals have committed to \( Var\left({H}_{1i}^S\right) \) prior to the realization of *ε*
_{
2
}. However, individual *i* can still alter the mix of occupational or industrial human capital in conjunction with decisions of whether to be an entrepreneur during period 2. We can characterize those choices as

#### Proposition 2.1 \( Cov\left({v}_{2i}^O,{v}_{2i}^E\right)>0. \)

High values of *λ*
_{
2
} will lead to broader human capital investments in period 2 as well as a higher likelihood of entrepreneurial status in period 2. Therefore, the theory requires that \( Cov\left({v}_{2i}^O,{v}_{2i}^E\right)>0 \).

#### Proposition 2.2

As the time gap between period 2 and 1 increases, \( {\theta}_S^E\to 0 \).

This prediction does not follow directly from our theory as it represents only two periods and there is no time gap between the two. However, in period 2 we have individuals changing their occupations. Case 1 and Case 4 individuals experience no loss of their period 1 human capital. However, Case 2 individuals moving from *E*
_{1} to *L*
_{2} will find that half of the human capital they generated in period 1 will be wasted. Case 3.B individuals moving from *L*
_{1} to *E*
_{2} will waste part of their period 1 investment in specialized human capital. Case 3.A individuals moving from *L*
_{1} to *E*
_{2} base their decision without regard to period 1 human capital investments. For these three cases, period 1 human capital investments become less tied to entrepreneurial status in period 2. This lost correlation will become even more evident as Period 2 lengthens and *H*
_{
2
} increases relative to *H*
_{
1
}. Note that occupational or sectoral work decisions will continue to be adjusted with the entrepreneurial decision in period 2, and so the correlation between *E*
_{2i
} and \( Var\left({H}_{2i}^O\right) \) will not diminish over time.

#### End of period 2

It is easier to examine evidence for Proposition 2.2 if we consider examining data at the end of period 2 after occupational or sectoral employment decisions have been made. We can then modify (3.1) as

where we are defining period 2 as composed of *T*
_{
i
} subperiods from the timing of school leaving until the time we observe occupational status. If period 1 human capital investments decay in value over time, whether because new information on entrepreneurial skills alters entrepreneurial trajectory or because human capital is subject to depreciation over time, \( \left(\frac{\partial q}{\partial \left(\frac{H_1}{H_2}\right)}>0\right) \), *ω*
_{
S1}
*>*0 and *ω*
_{
S2} < 0. On the other hand, the diversity of occupational experiences should increase the probability of entering entrepreneurship so that *ω*
_{
O
} > 0. Note that individuals who enter entrepreneurship early in their careers will have a relatively narrow mix of work experiences, and so one would expect the impact of occupational or sectoral job diversity to be biased downward. As we will see, that concern does not seem to alter our conclusions from empirical tests of the theory, perhaps because even those who plan to enter entrepreneurship at an early age will try to establish a mix of occupational experiences soon after leaving school.

### Data

The sample of alumni analyzed throughout this study is drawn from Iowa State University bachelor’s degree recipients between 1982 and 2006. By the end of 2007 when the survey was conducted, the sampling population consisted of 84,917 alumni. The sampling rate was approximately 24 percent. The total sample drawn was 25,025. We received 5,416 usable surveys for a response rate of 21.6 percent^{7}. The survey elicits information on all jobs held since graduating from ISU including whether the individual ever started a business. That survey information serves as the basis for our study of entrepreneurial entry. The ISU survey includes BA recipients from a land-grant institution that is obligated to accept applications from any resident that finished in the top half of his or her high school class. After excluding those who are still students or retired by the end of 2007, we find that 91% of alumni have consistent employment history after graduation. Among them, 88% have been laborers and 3% of students started a business in five years after graduation and have continued to be entrepreneurs until when surveyed. The remaining 9% of students switch between self-employment and employment. In particular, 7% of them worked as laborers right after graduation and then started a business five years later. Two percent of them were self-employed within five years after graduation but switched to employment later.

Compared to Stanford MBAs, our sample will reflect a much broader range of abilities, family incomes, and interests in business. In contrast, Stanford MBAs will be drawn atypically from the upper tail of distributions of socioeconomic status, cognitive ability, and business interests. At minimum, it is useful to examine the extent to which the JAT theory predictions extend to a less selective population that is also less naturally oriented toward entrepreneurship. For each alumni respondent to the ISU survey, we were allowed to merge in information from their academic record. The match worked very well, with only 3 out of 5,416 observations missing. The student’s transcript provides complete information on college major(s), coursework inside and outside the major, coursework in mathematics, science and business, and academic performance. The student record also adds information on gender, high school rank, and high school coursework.

The JAT theory predicts that those interested in entrepreneurship will select a more diverse academic program. Following Lazear, we define a variable *AC_SPEC*
_{
i
} to measure the degree of specialization in individual *i*’s academic program. The value is the number of courses in the major minus the average number of courses taken in other departments. This is an inverse measure of the variance in academic human capital investments \( Var\left({H}_{1i}^S\right). \) In Lazear’s analysis of Stanford MBAs, entrepreneurs had lower values of *AC_SPEC*
_{
i
}.^{8} Because different majors may have different curricular that may generate systematic differences in course diversity, in the following regressions, we control the fixed effect of students’ colleges. This makes students’ academic diversity comparable when holding course portfolio of college programs constant.

Table 1 shows the average levels of academic diversity for entrepreneurs and laborers by cohort. There are significant differences in academic diversity only for the most recent cohort which was surveyed within five years of graduation. For that group, nonentrepreneurs have two more courses inside their major than entrepreneurs. The differences diminish in magnitude and significance as time since graduation increases, consistent with one prediction from the theory that diversity in academic skills will be more relevant to entrepreneurial entry when not much time has elapsed since graduation.

We use two measures of the diversity of work experiences as our proxies for \( Var\left({H}_{1i}^O\right) \) referred to in equation (3B): *OCCUPATIONS*
_{i}, which represents the number of different occupational experiences since graduation, and *INDUSTRIES*
_{
i
}, which measures the number of different industries in which those jobs were located^{9}. Table 2 reports the average values of *OCCUPATIONS*
_{
i
} and *INDUSTRIES*
_{
i
} for entrepreneurs and wage workers. Entrepreneurs consistently have held more occupations and worked in more industries since graduation than non-entrepreneurs, although the difference is not always statistically significant. Note that individuals with successful entrepreneurial ventures will stop seeking other work, and so the bias in number of occupations would be against the JAT prediction that entrepreneurs would have more diverse work experiences^{10}.

Proposition 1.1 suggests that individuals with strong draws on entrepreneurial skill will have consistently broad academic and occupational experiences. As a result, we should see that those who select more varied academic programs will also have more varied work histories. The first-pass look at the data appears to be consistent with that expectation. In Table 3, we examine the occupational choices of alumni with the 25% most and 25% least diverse programs of study. Graduates from more narrowly focused majors also tend to have more specialized work careers. Graduates who had broader academic training have a slightly greater tendency toward more diverse work careers.

While the broad tendencies in the data appear to be consistent with the JAT theory, we need to examine whether the first-pass evaluations hold up to controls for other covariates that could affect decisions on academic and occupational choices. Summary statistics on those covariates are shown in Table 4. The sample statistics are reported by early entrepreneurs (those who opened a business within five years of graduation), later entrepreneurs, and non-entrepreneurs. Consistent with national data on the incidence of self-employment, 15.8% of the ISU alumni have started a business. Entrepreneurs were atypically male, from larger families, and from families that owned a business. Non-entrepreneurs were better students in high school but the two groups performed equally well in college. Entrepreneurs atypically studied agriculture or business, but significant fractions from each college became entrepreneurs. By the time of graduation, entrepreneurs are more likely to be married. Consistent with Tables 1 and 2, entrepreneurs worked in more occupations and industries and had broader academic programs.

### Empirical findings

#### Period 1: entering college

The model predicts that individuals will be planning their academic and occupational trajectories before they begin college, given knowledge of their potential entrepreneurial abilities. We test that proposition using equations 3(A-C). The model suggests that decisions on academic diversity \( Var\left({H}_{1i}^S\right) \), occupational diversity \( Var\left({H}_{1i}^O\right) \) and entrepreneurship *E*
_{
1i
} will be made jointly based on a vector of attributes *Z*
_{
i
} composed solely of information available to the individuals at the time of college entry. To operationalize the empirical construct, we proxy the dependent variables as a vector of dummy variables. \( Var\left({H}_{1i}^S\right) \) is indicated by a dichotomous variable *S*
_{
i
} = 1 if *AC_SPEC*
_{
i
} ≤ *AC_SPEC*
_{
25%
}, where *AC_SP EC*
_{
25%
} divides the measure of course concentration from the lowest 25% and the upper 75%. *S*
_{
i
} = 1 indicates that individual *i* has one of the 25% most diverse academic programs in the sample.

Similarly, \( Var\left({H}_{1i}^O\right) \) is indicated by a dichotomous variable *O*
_{
i
} = 1 if *OCCUPATIONS*
_{
i
} ≥ 2, which is the 75th percentile number of occupations. The variable *E*
_{
1i
} is alternatively defined as indicating whether individual *i* has ever started a business or whether individual *i* has ever started a business that was ultimately successful. We posit that the error terms \( {v}_i^k={\beta}_{\lambda}^k{\lambda}_{1i}+{\xi}_i^k,\kern0.5em k=S,\ O,E \); are distributed such that *λ*
_{1i
} ~ *N*(0, *σ*
^{2}), \( {\xi}_i^k\sim N\left(0,1\right) \) and \( Cov\left({\xi}_i^k,{\lambda}_{1i}\right)=0. \) Then the system 3(A-C) can be estimated using a trivariate probit specification^{11}.

The correlation coefficient between any two random errors out of the three equations is

A finding of *ρ*
_{
SO
} > 0, *ρ*
_{
SE
} > 0 and *ρ*
_{
OE
} > 0 is consistent with Proposition 1.1 that there is a common unobserved factor *λ*
_{1i
} that generates a positive correlation among the errors in the three decisions. That unobservable factor is consistent with an unobserved entrepreneurial skill. The signs and magnitudes of the parameter \( {\beta}_{\lambda}^S,\kern0.5em {\beta}_{\lambda}^O, \) and \( {\beta}_{\lambda}^E \) will show how and to what extent the unmeasured entrepreneurial human capital affects their skill investment portfolio and occupation choices. We can identify these parameters up to a constant of proportionality by imposing that \( {\beta}_{\lambda}^S = 1 \), a restriction that will preserve the sign and relative magnitudes of the *β*s.

Our estimates of \( {\beta}_{\lambda}^S,\kern0.5em {\beta}_{\lambda}^O, \) and \( {\beta}_{\lambda}^E \) will test for the validity of Proposition 1.2 that \( sgn\left({\beta}_{\lambda}^S\right)=sgn\left({\beta}_{\lambda}^O\right)=sgn\left({\beta}_{\lambda}^E\right). \) The model presumes that the three choices are subject to a common set of factors *Z*
_{
i
} that affects returns to all three choices similarly. The results are shown in Table 5. First, it is apparent that the error term parameters \( {\beta}_{\lambda}^O \) and \( {\beta}_{\lambda}^E \) are significantly positive, implying positive correlation coefficients *ρ*
_{
OE
}, *ρ*
_{
SO
} and *ρ*
_{
SE
}. As the effect of *λ*
_{
S
} is normalized at 1 for schooling diversity, the impacts of diverse occupational and industrial job experiences on entrepreneurial entry are even larger. There is a common unobservable attribute that drives academic, occupational and entrepreneurial choices, consistent with the model predictions of the effect of unobserved entrepreneurial skill.

There is also support for the proposition that there are common effects of individual attributes on the three choices. Males, those from larger families with more educated fathers and at least one parent who had started a business were more likely to become entrepreneurs, have a varied work history, and select a more diverse college curriculum. Higher high school class rank lowered the likelihood of all three decisions. Mother’s education had a negative effect in the two cases where the coefficients were significant. The only conflicting finding was for ethnic minority status, which raised the probability of entrepreneurship despite increasing both academic and occupational specialization. The overall evidence is that a factor that raises returns to entrepreneurship increases incentives to have diverse occupational and academic experiences as well, consistent with Proposition 1.2.

#### Period 2: leaving college

Upon leaving college, individuals decide whether to start a business immediately or later or accept employment from someone else. Receiving a high value of *λ*
_{
2
} will motivate individuals to make broader human capital investments in work experience. In the end, this leads to a higher likelihood of entrepreneurial status, consistent with Proposition 2.1^{12}. At the same time, the decision will be influenced by the diversity of the academic program, with the prediction from equation (3) and (4) that \( {\theta}_S^E>0 \) and \( {\theta}_S^o>0 \). As time goes by and individuals learn more about their entrepreneurial skill, we would expect the importance of the academic program to fall as additional occupational or industrial experiences gain in importance, consistent with Proposition 2.2.

We time the analysis in two ways, whether the individual starts a business within five years of graduating, which we refer to as early entrepreneurial entry. We then redo the analysis defining as lifetime entrepreneurs those who ever started a business after graduating. Academic diversity should be more important for early entry, and occupational or industrial diversity should matter more for lifetime entry.

Using the specification defined by equation (5) where sectoral employment decisions have been made after graduation, we estimate a logit model of entrepreneurship, including covariates during college and after college. Because older and younger alumni will have different opportunities to acquire occupations, we create a measure *AVGOCCUP*, which is *OCCUPATIONS* divided by years of work experience. The results are shown in Table 6. The first two columns examine early entrepreneurial entry, and the last two columns examine lifetime entry. More specialized academic programs (high values of *AC_SPEC*
_{
i
}) reduce the probability of starting a business within five years of graduation, consistent with Proposition 2.1^{13}. Evaluated at the sample mean of *AC_SPEC,* the marginal effect implies that having an additional course in the student’s major will reduce probability of starting a business by 0.11%. In terms of work experience, having an additional one more occupation per year will increase the probability of entrepreneurial entry within 5 years after graduation by 1.7%, again evaluated at the mean of *AVGOCCUP.* Industry diversity is not significant for early entrepreneurship. Note that even in the short period following graduation, entrepreneurs tend to also have more varied occupational and industrial job experiences than their classmates who engage in wage work.

Expanding the time frame to as many as 25 years after graduation depending on graduation date, the importance of academic diversity diminishes in magnitude and significance as suggested by Proposition 2.2. On the other hand, occupational and industrial diversity retains both magnitude and significance of their effects^{14}. The marginal effect of occupational diversity is 0.28, which implies a 5.6% increase in entrepreneurial entry from an additional occupation over the five years. Working in one more industry over the five years increased the probability of starting a business by 4.9%.

There are some interesting findings from regression results in Table 6 that are worth exploring. Men are significantly more likely to start a for-profit business than women. Marriage and ethnicity also increases likelihood of entrepreneurship. College GPA is only positively correlated with early entrepreneurship but not relevant in lifetime entrepreneurship. Students majoring agricultural and life science, design and human sciences are more likely to be entrepreneurs than those majoring in liberal arts. Higher high school rank lowers the probability of starting a business. High school rank is an observable signal of productivity for employers. Just as high school class rank raises the probability of college admission and merit scholarship (Cohn *et al.*, 2004), we would expect that it will also increase the wage that employers would offer. That raises the opportunity cost of becoming an entrepreneur.

In addition, family background is shown to be relevant to offspring’s entrepreneurship. If one of the parents owns a business, individual’s entrepreneur-propensity rises substantially. The mother’s and father’s education affects their children’s entrepreneurship in different directions. Father’s education significantly boosts individual entrepreneurial entry, but mother’s education does not. Our finding is consistent with Fairlie (1999), who uses father’s education as a proxy for wealth in the absence of a measure of parental wealth and finds that father’s education is positively related with children’s entry into self-employment. Mother’s education and growing up with both parents are both correlated with the intergenerational transmission of human capital (Currie and Moretti, 2003), and so their children may seek more specialization through professional or graduate education instead of entrepreneurship.

Having a close friend who starts a business reduces the entrepreneurial probability. This may seem counterintuitive, at first blush, but a similar result was reported by Lerner and Malmendier (2013). Their field experiment using MBA students found that having a high share of entrepreneurial peers decreases entrepreneurship. Perhaps observing the challenges of entrepreneurship faced by friends discourages entrepreneurial entry.

#### Is this positive correlation in human capital and occupation choices due to taste for variety?

We have interpreted the positive correlation in the errors of our entrepreneurship, academic diversity and job experience diversity equations as consistent with the existence of an unobservable managerial ability *λ* that would increase the probability of all these choices. Åstebro and Thompson (2011) and Oberschachtsiek (2009) argued that the positive correlation was not skill but due instead to a preference for variety which led to diverse academic and occupational choices.

We can examine this alternative explanation using questions included in the survey that elicit individual taste for variety. The first measure is the number of extra-curricular activities including sports, music, drama, academic clubs, 4-H/ FFA, or scouting in which the respondent participated in high school. The second measure is a binary variable that indicates a preference for nonconforming or unstructured activities or for doing things differently. As can be seen from the logit regression results in Table 7, these taste indicators do have some ability to explain entrepreneurship.^{15} In particular, individuals preferring to do things differently than to do things better are more likely to start a business. We replicated the tests using the number of all business started over the lifetime. As shown in the negative binomial regressions in the last three columns of Table 7, none of the implications change when we distinguish serial entrepreneurship from one-time entrepreneurs. Even after we control for measures of taste for variety, the measures of occupational variety and academic diversity retain the same effects that they had before. Our findings supporting the role of diverse skills in entrepreneurial choice are not driven by an underlying preference for variety.

#### Is this positive correlation in human capital and occupation choices due to risk aversion?

Entrepreneurs are believed to be willing to take risk. If risk aversion is correlated with diverse human capital investments strategies, our tests of the JAT mechanism will be subject to a spurious correlation due to omitted variable bias. In fact, Hsieh, Parker and Praag (2011) find that more risk averse individuals are more likely to invest in diverse skills and also to become entrepreneurs. It is clearly shown in Figure 1 that if *λ*
_{1} is just a little higher than the entrepreneurship threshold 2, *λ*
_{1} = 2 + *ϵ* where *ϵ* is positively close to zero, more risk averse individuals may want to equalize human capital investment in H_{1}, as long as the risk premium paid is smaller than \( \frac{H_1}{2}. \)

There is no direct measure of risk aversion or risk preference in the survey data. Following Lazear (2005), we include industry fixed effects to control for different standard deviations of income by industry or occupation. For each individual, we include dummy variables indicating the various industries and occupations the individual has worked. It is important to note that this method is likely to overcorrect for the role of missing tastes for risk in that the least risk averse may well invest in more diverse academic and occupational skills precisely because they do want to become entrepreneurs, consistent with the theory.

The survey elicited information on all past industries and occupations but did not specify the timing of those jobs. Consequently, we are not able to identify which industry and occupation experiences preceded entrepreneurship. For that reason, these regressions drop individuals who entered and left entrepreneurship, and only considers those who either are successful entrepreneurs or who never became entrepreneurs. In the young sample, this adjusted entrepreneurship measure includes entrepreneurs who are still operating the businesses five years after graduation. The lifetime adjusted entrepreneurship measure includes those still operating the business twenty-five years after graduation. Based on logit regressions from Table 6, Table 8 reports the augmented regression results, adding these risk preference factors. Dummy variables of industry fixed effect are jointly significant, indicating that individual-specific industry experiences matter for entrepreneurship. However, adding these controls for industry and occupation fixed effects do not affect the sign, magnitude or significance of any of our measures of academic or job diversity. Our previous conclusion that diverse skills lead to entrepreneurship as predicted by the JAT theory remains robust to these specification changes^{16}.

#### Do entrepreneurs earn more from skill diversity?

We interpret *λ* as an unobserved entrepreneurial ability that induces individuals to invest in a diversified skill set in anticipation of becoming an entrepreneur. The theory relies on two critical assumptions that are testable: switching from entrepreneurship to wage work will bring an income reduction due to wasted human capital investments; and entrepreneurs get an income premium from diverse skill sets that are not valuable to specialized workers. In this section, we test these hypotheses by analyzing Mincerian income equations. We report the regression results in Table 9.

We should emphasize that these tests are predicated on the observed decisions to switch occupations or to stay in the initial occupation. It is the act of switching occupations that leads to lost human capital investments, and so our estimate of the return to switching is conditional on that decision. The decision itself is based on unobservable negative shocks to the unobserved *λ*. Similarly, the decision to remain an entrepreneur is predicated on more favorable updated information on the magnitude of *λ*. Our estimates of these returns must use the observed decisions to move or stay in order for use to estimate the returns conditional on those choices.

The first column in Table 9 reports results without any covariate controls. We find a significant income reduction for those who switch from entrepreneurship to specialist status, while there is no significant earnings difference between persistent entrepreneurs and persistent laborers. After controlling for individual characteristics and state fixed effects in the second and third regressions, we find even greater evidence of earnings losses associated with switching out of entrepreneurship and large negative earnings losses from switching into entrepreneurship from wage labor. The latter finding is consistent with Case 3B in which those switching into entrepreneurship are unable to fully balance their skills and waste some of their specialized human capital investments from the first period. Persistent entrepreneurs and persistent laborers who fully utilize their skills, in theory, continue to earn comparable incomes when the controls are added.

In the last two columns, we examine the relationship between specialized and general skills and earnings by occupation. Column (4) focuses on the earnings of persistent laborers and column (5) examines the earnings of persistent entrepreneurs, respectively, and test whether entrepreneurs benefit from skill diversity more than specialists. As shown in the last two columns, individual entrepreneurs obtain a significant positive return to academic skill diversity (AC_SPEC), while persistent laborers do not. This confirms that individuals become entrepreneurs because their skill diversity generates higher entrepreneurial productivity, not because individuals have taste in variety, in which case we expect a negative return on skill diversity. Furthermore, experience in more industries is negatively related to laborer’s income but positively related to entrepreneur’s income. It confirms that entrepreneurs earn more from having more diverse work experience, but laborers maximize income from specialization. Therefore, we complete the test of hypotheses from the dynamic occupation choices model. And we confirm that higher level of unobserved entrepreneurial abilities induces individuals to consistently invest in human capital diversely and benefit from this diversity. Switching occupations due to exogenous shock will lower income because of sunk human capital that is not reversible.

## 3 Conclusion

This paper examines the theoretical predictions of the Lazear "Jack-of-all-Trades" model of entrepreneurship when multiple periods are allowed and then tests those predictions using data collected from a sample of Iowa State University bachelor’s degree recipients from 1982–2006. Several of the findings from Lazear’s (2005) paper using a sample of Stanford MBAs are confirmed using this broader sample of college graduates. Individuals selecting broader academic programs and that have more varied occupational and industrial work experiences are more likely to become entrepreneurs.

In the Lazear framework, the mechanism driving the positive correlation between academic and occupational choices and entrepreneurial entry is an unobservable entrepreneurial skill. Hence, the positive correlation between academic or occupational diversity and entrepreneurship is not causal but a reflection of a common missing variable that affects all choices in the same direction. This paper explores that possibility by treating choice of academic program, occupational path and entrepreneurship as joint decisions planned at the time of college entry. The results are broadly consistent with the theory.

Error terms in the three equations are positively correlated, consistent with the existence of a common unobservable factor that increases the likelihood of all three decisions. Furthermore, observable factors that raise the probability of one decision raise the probability of the other two as well in 12 of 15 instances. We view these results as strong confirmation of Lazear’s JAT theory.

We are also able to examine evidence of predictions from our extension of the Lazear theory to multiple periods. Most importantly, we find that broader academic programs raise the probability of entrepreneurial entry early in the career, but the effect dissipates over time as individuals gain additional information on their entrepreneurial skills. This finding is consistent with our simple extension of the Lazear JAT theory, further supporting the strength of the insight that entrepreneurs require broad training and workers require specialized training to be successful in their chosen occupational paths. Our study also echoes the finding of the seminal paper on entrepreneurial learning by Jovanovic (1982) that firms learn about their efficiency as they operate in the industry. In our study, though we use proxy measures of preference which may introduce additional noise, we still find evidence of an unobserved entrepreneurial ability affecting occupational choice, and the evidence persists even after controlling for taste for variety and risk aversion.

We see two possible interpretations of our findings. One is that individuals intentionally make investment in human capital, including both skills acquired in school and in the workplace, conditional on their knowledge of their own entrepreneurial skill, which is not observed by others. The other is that there might be some unobserved alternative factor that induces individuals to make more diverse human capital investments. Academic diversity then becomes an endowment that raises the probability of starting a business. Though investment in diversity of human capital is not initially triggered by entrepreneurial aspirations, the accumulated diverse skills equip these individuals to enter entrepreneurship.

## Endnotes

^{1}If instead the first period skills are exogenously determined and only the second period occupation decision is modeled, we will still reach similar conclusions.

^{2}In Lazear (2005), *λ* is interpreted as entrepreneurial premium, representing various possible unobservables such as entrepreneurial abilities, or even envisioning of entrepreneurial abilities.

^{3}We assume that the cost of investing in two skills is not differentiated, which leaves individuals with choices in skills driven by return to occupation types.

^{4}Details of solving equation (1) could be available upon requesting authors.

^{5}This is an alternative rationale for why entrepreneurs earn less than equally skilled non-entrepreneurs, as found by Hamilton (2000). Hamilton argued that entrepreneurs accept lower income because they get utility from the freedom of running their own businesses. This argument suggests entrepreneurs may also earn less on average if their human capital investments anticipating success as entrepreneurs are subject to depreciation if they switch to wage work.

^{6}
\( \frac{\partial q}{\partial \left(\frac{H_1}{H_2}\right)} \) has an ambiguous sign when *H*
_{
2
}
*< H*
_{
1
}, depending on the shape of density function *g*(⋅). If *g*(⋅) is highly skewed right, \( \frac{\partial q}{\partial \left(\frac{H_1}{H_2}\right)} \) may become negative. However, conditional comparative statics are unambiguous. \( \frac{\partial Prob\left({E}_2=1\Big|{E}_1=1\right)}{\partial \left(\frac{H_1}{H_2}\right)}>0 \) and \( \frac{\partial Prob\left({E}_2=1\Big|{L}_1=1\right)}{\partial \left(\frac{H_1}{H_2}\right)}<0, \) indicating starting a business is harder when old for an individual who has specialized human capital investment when young. If *H*
_{1} is measured by academic experience and *H*
_{2} is measured by work experience, we are reasonably more interested in the case of *H*
_{2} ≥ *H*
_{1}, as in the following empirical analysis.

^{7}We use sample weights to correct for differences in probability of response between survey years and between alumni within survey years. We construct weights so as to relate the number of respondents in each college-cohort cell to the number in the universe. Let *N*
_{
t
} be the total number of students who graduated from Iowa State University with a Bachelor’s degree in year *t*. Let *n*
_{
jt
} be the number of alumni who graduated from college *j* in year *t*. There are six colleges: Agricultural & Life Sciences, Business, Design, Engineering, Human Sciences and Liberal Arts & Sciences. The proportion of these alumni out of the graduates from ISU in year *t* is *n*
_{
jt
}/ *N*
_{
t
}. The corresponding number of alumni in our sample who graduated from college *j* in year *t* is *s*
_{
jt
}. Each individual in our sample is then assigned with a sampling weight *n*
_{
jt
}/*s*
_{
jt
} such that the weight will represent the number of total alumni from college *j* in year *t*.

^{8}We also created an academic Herfindahl index measured as \( {\displaystyle \sum }{\mathrm{s}}_{\mathrm{ij}}^2 \), where \( {\mathrm{s}}_{\mathrm{ij}}^2 \) is the share of credits earned in major *j* by individual *i*. The simple correlation between the Herfindahl measure of coursework concentration and *AC_SPEC*
_{
i
} was 0.69, and qualitative results were similar. However, some of the empirical models using the Herfindahl measure ran into convergence problems, and so we opted for *AC_SPEC*
_{
i
}
*.*

^{9}See the appendix for detailed information about specific industries and occupations in the survey.

^{10}In measuring prior occupational and industrial experiences, we do not differentiate between single and serial entrepreneurs. Thus, while wage-workers will commonly change jobs and gain additional experiences, our entrepreneurs do not. This means that our measure of variety of industrial and occupational experiences will be biased downward for entrepreneurs but not wage-workers. In our sample, almost one-quarter of our entrepreneurs started more than one business. The implication is that our empirical tests will be biased against finding greater variety of occupational and industrial experiences for our entrepreneurs. As will become apparent, despite this greater hurdle against finding results consistent with the Lazear “Jack-of-all-Trades” hypothesis, our empirical work generally supports the theory.

^{11}We use the Generalized Linear Latent and Mixed Models procedure in STATA to estimate the model. It uses the Newton—Raphson method and adaptive quadrature to approximate the likelihood function by numerical integration (Rabe-Hesketh et al. 2004). The model also takes into account sample weights in order to obtain robust standard errors (Rabe-Hesketh and Skrondal 2006).

^{12}The positive correlation between entrepreneurship and work experience diversity is embedded in the Tri-variate probit specification in Table 5. In fact, we joint estimate entrepreneurship and occupational choices, treating academic achievement as given, using a bivariate probit specification of equation (3) and (4). Regression results are shown in Additional file 1: Table S3, consistent with the proposition \( Cov\left({v}_{2i}^O,{v}_{2i}^E\right)>0. \)

^{13}If individuals are successful at their jobs, they will stay or get promoted within firms. Neither *OCCUPATIONS* nor AVGOCCUP could capture the diversity or the expertise within industries. To address this industry-specific diversity, we create an alternative variable, namely, average number of occupations per industry. We find that the majority of individuals stay in one or two industries and get promoted within or transfer to other jobs within the same industry. Using this newly created variable, regression results in Table 6 are not qualitatively changed.

^{14}In the regression above, we exclude controls for advanced degrees. Pursuing advanced education is endogenous in occupation choices because an advanced degree is just a means of gaining even more specialization for individuals who want to work for wages rather than becoming an entrepreneur. Even for those who may entertain thoughts of entrepreneurship, graduate school delays asset accumulation which may be necessary to funding a start-up. Nevertheless, one might be concerned that excluding advanced degrees leads to missing variables bias, which may cause greater concern than the endogeneity. Therefore, we reestimated the specification in Table 6 including information on advanced degrees including Master’s; PhD and Professional degrees. A second specification only included the alumni who completed their schooling at the Bachelor’s degree. All our main conclusions were robust to these alternate specifications.

^{15}In Table 7, we also include the number of business started as the dependent variable. Taste for variety may be not only positively correlated with switching to entrepreneurship but also with diversifying entrepreneurship. The measure is highly skewed, with 84% of individuals never starting a business, 12% starting only one business and 4% starting at least two businesses. Results do not change when we use a negative binomial regression to accommodate the highly skewed dependent variable.

^{16} We should note that specifying specific industry fixed effects is likely a misspecification due to the endogeneity of the industry choice. If some industries nurture future entrepreneurs more than others, future entrepreneurs will select those industries, and thus industry and entrepreneurship are joint decisions. Nevertheless, we felt it more useful to replicate this test following prior work, but to caution about the possible bias.

## References

Åstebro T, Thompson P (2011) Entrepreneurs: jacks-of-all-trades or hobos?. Res Policy 40(5):637–649

Blau DM (1987) A time-series analysis of self-employment in the United States. J Polit Econ 95(3):445–466

Borjas G, Bronars S (1989) Consumer discrimination and self-employment. J Polit Econ 97(3):581–605

Cohn E, Cohn S, Balch DC, Jr JB (2004) Determinants of undergraduate GPAs: SAT scores, high-school GPA and high-school rank. Econ Educ Rev 23:577–586

Currie J, Moretti E (2003) Mother's education and the intergenerational transmission of human capital: evidence from college openings. Quart J Economics VCXVIII 4:1495–1532

Dunn T, Holtz-Eakin D (2000) Financial capital, human capital, and the transition to self-employment: evidence from intergenerational links. J Labor Econ 18(2):282–305

Evans DS, Leighton LS (1989) Some empirical aspects of entrepreneurship. Am Econ Rev 79(3):519–535

Fairlie RW (1999) The absence of the African-American owned business: an analysis of the dynamics of self-employment. J Labor Econ 17(1):80–108

Fairlie RW, Meyer BD (2000) Trends in self-employment among white and black Men. J Hum Resour 35(4):643–669

Fairlie RW (2002) Drug dealing and legitimate self-employment. J Labor Econ 20(3):538–567

Fairlie RW, Robb A (2007) Families, human capital, and small business: evidence from the characteristics of business owners survey. Ind Labor Relat Rev 60(2):225–245

Hamilton B (2000) Does entrepreneurship Pay? an empirical analysis of the returns to self- employment. J Polit Econ 108(3):604–631

Holtz-Eakin D, Joulfaian D, Rosen HS (1994) Sticking It Out: entrepreneurial survival and liquidity constraints. J Polit Econ 102(1):53–75

Hsieh C, Parker SC, van Praag M (2011). Risk, Balanced Skills and Entrepreneurship. IZA Discussion Paper No. 6200.

Iyigun M, Owen A (1998) Risk, entrepreneurship, and human-capital accumulation. AEA Papers Proc 88(2):454–457

Jia R, Lan X (2013) Red capitalism: cadre parents and entrepreneurial children in china. Cheung Kong GSB working paper

Jovanovic B (1982) Selection and the Evolution of Industry. Econometrica 50(3):649–670

Lazear E (2004). Balanced Skills and Entrepreneurship. The American Economic Review Papers and Proceedings 94(2).

Lazear E (2005) Entrepreneurship. J Labor Econ 23(4):649–680

Lechmann D, Schnabel C (2014) Are the self-employed really jacks-of-All-trades? testing the assumptions and implications of Lazear’s theory of entrepreneurship with German data. Small Bus Econ 42(1):59–76

Lerner J, Malmendier U (2013) With a Little Help from My (Random) Friends: Success and Failure in Post-Business School Entrepreneurship. Rev Financ Stud 26(10):2411–2452

Lucas J, Robert E (2002) Lectures of Economic Growth. Harvard University Press, Cambridge, MA

Marino M, Parrotta P, Pozzoli D (2012) Does labor diversity promote entrepreneurship?. Econ Lett 116:15–19

McMillan J, Woodruff C (2002) The central role of entrepreneurs in transition economies. J Econ Perspect 16(3):153–170

Murphy KM, Schleifer A, Vishny RW (1991) The allocation of talent: implications for growth. Q J Econ 116(2):503–530

Oberschachtsiek D (2009) “What makes a ‘jack-of-all-trades’?” IAB-discussion Paper 10/2009

Rabe-Hesketh S, Skrondal A, Pickles A (2004) GLLAMM Manual, U.C. Berkeley Division of Biostatistics working paper series

Rabe-Hesketh S, Skrondal A (2006) MultilevelModeling of complex survey data. J R Stat Soc 169:805–827

Romer PM (1986) Increasing returns and long-Run growth. J Polit Econ 94(5):1002–1037

Romer PM (1990) Endogenous Technical Change. J Polit Econ 98(5):71–102

Rosen S (1983) Specialization and human capital. J Labor Econ 1(1):43–49

Schultz TW (1988) On investing in specialized human capital to attain increasing returns. In: Ranis G, Schultz W (eds). Blackwell Publishers, The State of Development Economics Cambridge, MA, pp 339–352

Silva O (2007) The Jack-of-All-Trades entrepreneur: Innate talent or acquired skill?. Econ Lett 97:118–123

Wagner J (2006) Are nascent entrepreneurs ‘Jack-of-all-trades’? A test of Lazear’s theory of entrepreneurship with German data. Appl Econ 38:2415–2419

## Acknowledgments

We gratefully acknowledge financial and in-kind support from the Iowa State Foundation, the Iowa State Alumni Association, the Iowa State Registrar’s Office, the Pappajohn Center for Entrepreneurship, and the Iowa State Agricultural Entrepreneurship Program. We thank the editor and the reviewers for their thorough review and highly appreciate the comments and suggestions. All errors are ours.

Responsible editor: Pierre Cahuc.

## Author information

### Affiliations

### Corresponding author

## Additional information

### Competing interests

The IZA Journal of Labor Economics is committed to the IZA Guiding Principles of Research Integrity. The authors declare that they have observed these principles.

## Additional file

### Additional file 1: Table S1.

Employment distribution of entrepreneurs and non-entrepreneurs across industries. **Table S2.** Employment distribution of entrepreneurs and non-entrepreneurs by occupations. **Table S3.** Bivariate probit model of entrepreneurship in late career.

## Rights and permissions

## About this article

### Cite this article

Orazem, P.F., Jolly, R. & Yu, L. Once an entrepreneur, always an entrepreneur? The impacts of skills developed before, during and after college on firm start-ups.
*IZA J Labor Econ* **4, **9 (2015). https://doi.org/10.1186/s40172-015-0023-7

Received:

Accepted:

Published:

### JEL

- J24

### Keywords

- Entrepreneurship
- Jacks-of-all-trades
- Educational experiences
- Working experience
- Entry