This study uses the hedonic wage method to estimate the value of statistical life (VSL) in Chile and then extrapolates this value to different Latin American countries. The data are obtained from the National Socioeconomic Characterization Survey (Encuesta de Caracterización Socioeconómica Nacional, CASEN 2013), which includes information on socioeconomic and labor variables at the individual level. Records of fatal and nonfatal occupational risk in each economic sector are obtained from the Superintendency of Social Security (Superintendencia de Seguridad Social). The results of the best hedonic wage estimate for the Chilean case (which corrects for endogeneity and selection bias) show that the VSL is US$3.7 million, with a confidence interval of 95 percent ranging between US$3.4 million and US$4.0 million. A meta-analysis that relates the VSL to GDP per capita is conducted to extrapolate the findings to other Latin American countries, with average values ranging from US$0.01 million for Haiti to US$5.2 million for Puerto Rico.
Este estudio utiliza el método de salarios hedónicos para estimar el valor estadístico de la vida (VEV) en Chile, y luego extrapola este valor a diferentes países latinoamericanos. Los datos son obtenidos de la Encuesta de Caracterización Socioeconómica Nacional CASEN 2013 que incluye información sobre variables socioeconómicas y laborales a nivel individual, mientras que los registros de riesgo laboral fatal y no fatal en cada sector económico se obtienen de la Superintendencia de Seguridad Social. Los resultados de la mejor estimación de salarios hedónicos para el caso chileno (que corrige por endogeneidad y sesgo de selección) muestran que el VEV es US$ 3.7 millones, con un intervalo de confianza al 95 por ciento que varía entre US$3.4 millones y US$4.0 millones. Para la extrapolación a otros países latinoamericanos se realiza un meta-análisis que relaciona el VEV con el PIB per cápita, obteniendo valores promedio que varían entre US$0.01 millones para Haití y US$5.2 millones para Puerto Rico.
The value of statistical life (VSL) is the marginal willingness to pay for (or the marginal willingness to accept) marginal risk reductions in a given context (environmental pollution, road safety, and occupational safety, among others), but it does not correspond to the ex-post value of the saved lives. Although from ethical and moral points of view, for many people, making an estimate of this type is questionable, in reality, there are certain situations in which this value is indeed quantified, particularly those in which individuals are willing to accept greater or lesser exposure to risk due to the tradeoff between the risk of mortality and money (Gentry and Viscusi 2016). For example, this value is useful for the cost-benefit analysis of projects that may aim to reduce levels of accidents, illness, or mortality. Therefore, having an estimate of VSL contributes greatly to decision-making, especially in low-income countries, where such studies are typically not performed (Hammitt and Robinson 2007).
The most commonly used approaches to quantifying VSL are the revealed preference approach, typically known as the hedonic wage method (which uses labor market information to relate the level of remuneration and the risk to which workers are exposed), and the stated preference approach (in which people are asked directly through surveys their willingness to pay for different hypothetical reductions in the level of risk). According to Viscusi and Aldy (2003), most studies in the United States are based on labor market information using the hedonic wage method, whereas in Europe, the emphasis is on using the stated preference approach. Most hedonic wage studies use cross-sectional data; however, recently, the use of panel data (Schaffner and Spengler 2010) has been emphasized, in addition to some other aspects, such as making differential estimates of VSL by type of risk (Scotton and Taylor 2011) or according to age groups (Evans and Schaur 2010), as well as the disaggregation of risk by industry and occupation (Riera Font, Ripoll Penalva, and Sbert 2007).
In many developing countries, the information needed to use one of these methods is not available, so a good alternative approach for the VSL is to extrapolate estimates from other countries (mainly developed) by relating the VSL to the GDP per capita of each country. For example, through a meta-analysis, Miller (2000) estimates a VSL of US$1.2 million for Argentina, US$0.7 million for Brazil, US$0.7 million for Chile, US$0.4 million for Peru, US$0.8 million for Uruguay and US$0.5 million for Venezuela (all values correspond to 1995 dollars). Lindhjem et al. (2011) performed a meta-analysis using previous VSL estimates for thirty-eight countries (all included values using the declared preference approach). These authors report an average VSL of US$6.0 million. When classified according to the context of the study, the average VSL correspond to US$9.0 million for environmental pollution, US$6.9 million for road safety and US$4.0 million for health.
In the case of Chile, some studies use the stated preference approach, but only one previous study uses the hedonic wage method. This last study was carried out by Parada-Contzen, Riquelme-Won, and Vasquez-Lavin (2013), who estimate a VSL of US$12.8 million after correcting for endogeneity and selection bias. This estimate is quite high in comparison to other developing countries and even higher than in some developed countries.1 This situation is not unusual because, although the concept of the value of statistical life is well established and widely used in economics, there is still controversy over the apparent instability in estimates of excessively large or small values (Viscusi and Aldy 2003). In this sense, some theoretical studies have noted that the potential bias of the estimates arises due to omitted variables (Hwang, Reed, and Hubbard 1992; Shogren and Stamland 2002). From an empirical perspective, Kniesner et al. (2007) demonstrate how the use of the best available data (panel data and risk level with high disaggregation) and the best econometric practices can determine the estimated VSL in previous studies.2
This situation motivated the realization of the present study, which uses more updated data with more explanatory variables and new instrumental variables to provide new evidence to clarify if the VSL for Chile estimated with the hedonic wage method is significantly different from the value of other countries with similar GDPs per capita and if the result of the only previous study can be attributed to data and/or methodological problems. Specifically, the contribution of this paper is in the line of demonstrating that the use of relevant instrumental variables3 that meet the exogeneity requirement makes it possible to correct for the problem of the endogeneity of risk and to improve the previous VSL estimates for the case of Chile.
When the available information is cross-sectional, the hedonic price method uses a linear regression, which represents the relationship between the wage level and the explanatory variables. The general model is as follows:
where In(wi) is the natural logarithm of the wage, H corresponds to the vector of personal characteristics, Ji represents the vector of the characteristics of the work, Li represents the vector of the characteristics of the firm, Gi represents the vector of geographical variables, ri corresponds to fatal risk, and pi corresponds to nonfatal risk. In turn, the vectors β, α, θ, and δ and the scalars c, γ and τ correspond to the parameters estimated in the regression, whereas ei is the error term. The subscript i indicates that the information corresponds to the i-th individual.
However, if there are unobservable variables that are correlated with one of the variables included in the statistical model (for example, risk aversion is not an observable variable for the researcher), the parameters estimated by the ordinary least squares method (OLS) will be biased and inconsistent. In relation to labor risk variables, what is relevant is not the risk to which the individual is exposed but the individual’s perception of the risk. This is why in the literature, the use of instrumental variables is suggested to estimate the perceived risk of individuals related to their work, which would reduce bias and inconsistency due to endogeneity.
If there are several instrumental variables to correct the endogeneity of one or several explanatory variables, the method of least squares in two stages (2SLS) can be used. In the first stage, the predicted values of the endogenous explanatory variables (ri and pi) are obtained from a regression related with the other exogenous explanatory variables and the instrumental variables. In the second step, a regression is generated through the OLS method of the variable In(wi) with respect to the exogenous explanatory variables and the estimated values of the endogenous explanatory variables. Specifically, in this case, the predicted value of nonfatal and fatal risk can be obtained with the following regressions:
where Si is a vector of instrumental variables that determine the risk of the individual, c1 and c2 are constants, ς, σ, χ, ψ and φ1 correspond to the parameter vectors estimated for the nonfatal risk regression, and ω, ξ, ϑ, κ, and φ2 correspond to the parameter vectors estimated for the fatal risk regression. Finally, μi and vi correspond to the random errors of the respective regressions.
Another problem related to the nature of cross-sectional data in studies to estimate the VSL is the so-called selection bias, which arises when the sample used to perform the regression is not completely random. The problem is that it is intended to estimate the wage offer equation for “all” individuals of working age, regardless of whether the individual is working. However, data related to the wage offer are observable only for those individuals who are currently working. To solve this problem, Heckman (1979) proposed a method known as Heckit, which proposes a regression model that consists of two related equations to correct the bias due to the self-selection of the sample.
where the latent variableis greater than zero if the labor offer is observed in the data (yi = 1) or less than zero otherwise (yi = 0). Furthermore, it is assumed that the errors ei and ηi have a bivariate normal distribution. From these assumptions, it can be shown that the expectation of conditional equation (5) to which labor participation is observed is as follows:
φ(⋅) corresponds to the probability density function and Φ(⋅) refers to the cumulative distribution function, both estimated with a Probit model. In addition, for simplicity, the coefficient ρσe can be called βλ because it is the coefficient that accompanies the estimate of the inverse Mills ratio, λi. Rearranging equation (6) yields the following:
Once the model is presented, the estimation of the parameters of interest is carried out with a two-step procedure or with maximum likelihood routines.
Additionally, instrumental variables can be included to estimate if some of the explanatory variables are assumed to be endogenous. In this case, the procedure is known as Heckit in two stages with endogenous variables (Heckit 2SLS).
From the review of several studies of hedonic salaries published in the last two decades, it was possible to determine the explanatory variables that are commonly included in this type of regressions.
As seen in Table 1, several categories of variables associated with personal characteristics, the characteristics of firms, labor information, and geographic variables are included. In the case of Chile, these variables are obtained from the CASEN survey performed in 2013.4
|Source (year)||Country||Number of personal characteristics||Number of variables with labor information||Number of characteristics of firms||Geographical Variables||Labor risk by economic sector||Labor risk by occupational category|
|Siebert & Wei (1994)||UK||10||3||3||Yes||Yes||Yes|
|Lanoie, Pedro & Latour (1995)||Canada||10||1||2||No||Yes||Yes|
|Sandy & Elliot (1996)||UK||10||3||3||No||Yes||Yes|
|Miller, Mulvey & Norris (1997)||Australia||9||1||1||Yes||Yes||Yes|
|Siebert & Wei (1998)||Hong Kong||5||0||0||No||Yes||No|
|Meng & Smith (1999)||Canada||8||2||2||Yes||Yes||Yes|
|Liu & Hammitt (1999)||Taiwan||5||2||1||No||Yes||Yes|
|Arabsheibani & Marin (2000)||UK||7||0||1||No||No||Yes|
|Sandy et al. (2001)||UK||10||3||3||No||Yes||Yes|
|Baranzini & Ferro Luzzi (2001)||Switzerland||8||4||4||Yes||Yes||No|
|Riera Font, Ripoll Penalva & Sbert (2007)||Spain||13||3||5||Yes||Yes||Yes|
|Schaffner & Spengler (2010)||Germany||9||2||2||No||Yes||Yes|
|Evans & Schaur (2010)||USA||7||1||0||Yes||Yes||Yes|
|Scotton & Taylor (2011)||USA||7||2||3||Yes||Yes||Yes|
|Parada-Contzen, Riquelme-Won & Vasquez-Lavin (2013)||Chile||15||5||4||Yes||Yes||No|
It is also necessary to include variables associated with labor risk (fatal and nonfatal), which in Chile can be obtained from the records of the Social Security Superintendence (Superintendencia de Seguridad Social). According to data from 2013, the sectors with the highest mortality rate are mining (19.5 per 10,000 workers), transport and communications (17.5 per 10,000 workers), and construction (10.3 per 10,000 workers), whereas the sectors with the highest levels of labor accidents are the manufacturing (6.2 per 100 workers), transport and communications (6.0 per 100 workers), and agriculture (5.4 per 100 workers). In addition, the sector with the lowest accident rate is mining (1.6 per 100 workers).
Table 2 presents the description of all the explanatory variables included in the present research.
|Lnwage (Chilean pesos)||Natural logarithm of wage||12.477||0.819|
|Schooling (years)||Schooling in years||10.289||4.231|
|Age years)||Age in years||35.452||22.403|
|Exper (years)||Experience in years||23.916||15.519|
|Exper2 (years 2)||Squared experience||812.830||879.755|
|Ethnicity||If you belong to an indigenous ethnic group||0.128||0.334|
|LaborExp (years)||Working age in years||8.539||10.124|
|Workh (hours)||Hours worked per week||45.961||58.029|
|Full time||If the job is full time||0.264||0.441|
|Indcontract||If the person has an indefinite contract||0.221||0.415|
|Training||If the person has any type of training||0.072||0.258|
|Employer||If the person is an employer||0.008||0.090|
|Indep||If the person is an independent worker||0.083||0.276|
|Jobcategory1||Executive member or legislative power||0.017||0.130|
|Jobcategory2||Professional, scientific or intellectual||0.038||0.190|
|Jobcategory5||Service or trade worker||0.065||0.246|
|Jobcategory6||Farmer or agricultural worker, fishing||0.031||0.174|
|Jobcategory7||Official, operator, craftsman of mechanical arts||0.063||0.243|
|Jobcategory8||Machine installation operator||0.039||0.195|
|Extrahours||Number of extra hours||0.025||0.158|
|Night shift||If the person works night shifts||0.258||0.438|
|Numworkersf1||Number of employees in the firm (1)||0.067||0.250|
|Numworkersf2_5||Number of employees in the firm (2 to 5)||0.046||0.209|
|Numworkersf6_9||Number of workers in the firms (6 to 9)||0.017||0.129|
|Numworkersf10_49||Number of workers in the firms (10 to 49)||0.045||0.206|
|Numworkersf50_199||Number of workers in the firms (50 to 199)||0.033||0.179|
|Numworkersf200||Number of workers in the firms (200 or more)||0.104||0.305|
|Region6||Liberian Bernardo O’Higgins Region||0.076||0.264|
|Region10||Los Lagos Region||0.060||0.237|
|Region12||Magallanes Region and the Chilean Antarctic||0.027||0.162|
|MetropolitanRegion||Metropolitan Region of Santiago||0.168||0.374|
|Region14||Los Ríos Region||0.053||0.224|
|ExtMigrat||If the person is a foreigner||0.007||0.081|
|IntMigrat||If the person has changed city in the last 5 years||0.071||0.257|
|Fatalrisk||Fatal risk rate (deaths per worker)||6.96E-04||5.52E-04|
|Non-fatalrisk||Nonfatal risk ratio (injuries per 100 workers)||4.826||1.210|
Moreover, it is necessary to incorporate instrumental variables to solve the problem of the endogeneity of labor risk (fatal and nonfatal).
According to Garen (1988), the instrumental variables that should be included in this type of study correspond to the nonlabor income and factors correlated with the perceived risk in the work but that do not explain the wage (see Table 3). Therefore, variables include: a dummy variable that takes a value of 1 if the partner of the individual has some type of disability (Disabhome), the nonlabor income in Chilean pesos (Nonlabincome), the number of children under six years of age (Numberkids6), a variable that determines the interaction between gender and children under six years old (Genderkids6), a dummy variable that takes a value of 1 if the individual is married (Married), the years of schooling of the couple (Coupleschooling), a dummy variable that takes a value of 1 if the individual’s partner works (Coupleworks), the number of people who are economically dependent on the household (Peoplehome), a dummy variable that takes a value of 1 if the individual has a life insurance (Lifeinsurance), and another dummy variable that takes a value of 1 if the individual lives with his partner, regardless of whether he is married (Withcouple). These are proxy variables of risk aversion that can affect the desire to have a safer job.
|Instrumental variables||Description||Mean||Standard deviation|
|Numberkids6||Number of children under 6 years||0.155||0.436|
|Genderkids6||Variable that relates gender and children under 6 years||0.061||0.287|
|Disabhome||If the partner has any type of disability||0.031||0.174|
|Married||If the person is married||0.283||0.451|
|Withcouple||If the person lives with his/her partner||0.401||0.490|
|Coupleschooling||Schooling of the couple in years||1.988||4.397|
|Coupleworks||If the couple works||0.182||0.386|
|Peoplehome||Individuals who are financially dependent on the worker individual||4.089||1.790|
|Nonlabincome||Nonlabor income in Chilean pesos||23909||116786|
|Lifeinsurance||If the person has life insurance||0.044||0.205|
|VI_Largefirms||Proportion of large firms by economic sector||1.902||1.699|
|VI_Mediumfirms||Proportion of medium-sized firms by economic sector||3.588||2.217|
|VI_smallfirms||Proportion of small firms by economic sector||22.729||8.254|
In addition, Angrist and Krueger (2001) state that the inclusion of labor market variables is a useful way to achieve identification with the method of instrumental variables. For this reason, the proportion of firms by size by economic sector is considered as instruments, considering small firms (VI_smallfirms), medium firms (VI_mediumfirms), and large firms (VI_largefirms); in this case, micro firms are the control group. These variables are included because in Chile, a relationship has been observed between the size of the firms and the rate of labor accidents,5 they reflect the characteristics of the labor market, and the workers in economic sectors with a greater proportion of small firms could have less bargaining power to alter their wages, so it is assumed that the requirement of exogeneity would be met.
After estimating the parameters in the regressions, it is possible to calculate the VSL for Chile with the following equation:
wherecorresponds to the average monthly wage, which is multiplied by 12 to obtain the annual average wage, and γ corresponds to the estimated parameter of the fatal risk. In addition, to make the results of this study comparable with previously published international estimates, conversion of values to 2013 dollars is performed.
The empirical literature for developing countries is scarce in this area, so there are no estimates for individual countries. This has led to suggesting the transfer of the VSLs from countries with estimates to countries that do not have them. The most common approach to transfer benefits is to assume that the ratio of VSL relative to GDP per capita is constant across countries, which implies assuming an income elasticity equal of 1.0. However, recent studies state that an income elasticity equal to 1.0 may be inadequate for low-income countries, so Hammitt and Robinson (2011) suggest using an income elasticity of 1.5 to provide a range of values for VSLs in countries of low and middle incomes. Another approach to extrapolate the results is to relate the VSL to each country’s GDP per capita by performing a meta-analysis (see Miller 2000; De Blaeij et al. 2003; Bellavance, Dionne, and Lebeau 2009; Hammitt and Robinson 2011).
Therefore, after estimating the VSL for Chile, this value will be included along with estimates previously published in scientific journals for different countries that also use the hedonic wage approach in order to extrapolate the VSL for other Latin American countries.
Different statistical methods were used to estimate the VSL for Chile (OLS, 2SLS, Heckit, and Heckit 2SLS).6 Most of the estimated parameters are significant at 1 percent, except for certain dichotomous variables related to firm size, type of occupation, and geographical variables. Moreover, the coefficients related to schooling, experience, training, and contract type show expected magnitudes and signs in relation to what the theory postulates and what has been observed in other studies of hedonic wages. In particular, the estimated coefficient for the educational variable has a magnitude between 0.037 and 0.049, which would indicate that one year of schooling increases wages approximately between 3.7 percent and 4.9 percent. Another variable to be highlighted is gender, which was positive in the estimates that did not correct for selection bias; this would indicate that men earn between 25.9 percent and 31.9 percent more than women. However, this gap is reduced (between 15.2 percent and 20.6 percent) when estimating the Heckit and Heckit 2SLS models, which correct the selection bias associated with women tending to participate less in the labor market.
In relation to the fatal risk parameter, this proved to be positive and significant at 1 percent in all estimates. However, there is a considerable difference in the estimated magnitudes; for example, the parameters estimated through the OLS and Heckit were found to be less than one third of the values estimated through the 2SLS and Heckit 2SLS method.
In contrast, the parameter of nonfatal risk was found to be significant in all the estimates, with a negative sign, contrary to what was expected. However, this result is also observed in other studies such as Riera Font, Ripoll Penalva, and Sbert (2007) and Arabsheibani and Marin (2000). In this case, the negative sign could be attributed to the fact that in Chile, the mining sector pays the highest average wages and presents a high fatal risk but also less nonfatal risk with respect to other economic sectors. Furthermore, nonfatal risk data may not be totally useful in this kind of estimation, even with better instrumental variables, because typically in official statistics serious accidents are presented together with nonserious ones.
At the same time, it can be observed that in the 2SLS and Heckit 2SLS estimates most of the estimated parameters are not sensitive to the inclusion of instrumental variables, except the coefficients associated with the variables related to fatal and nonfatal risk. In addition, the R7 values calculated are similar, with a magnitude close to 0.45, which is common in hedonic wage studies.
In the case of estimates with instrumental variables, their validity must be tested because the stronger the relationship between an instrumental variable and the endogenous explanatory variable(s) are, the better the instrument is. In addition, it is required that the instrumental variable is not correlated with other variables that affect the outcome (exogenous condition). These requirements ensure that the instrument can estimate parameters in an unbiased and consistent way.
Most of the included instrumental variables were significant at 1 percent or 5 percent, but only the instrument inclusion related to the proportion of firms by size according to economic sector significantly improved the regression adjustments for the variables of fatal risk (R2 = 0.43) and nonfatal risks (R2 = 0.45). This is important because if the instruments are poorly correlated with the endogenous explanatory variable, the parameters estimated by the 2SLS method may be even worse than using the OLS method. If there is only one endogenous regressor variable and the instrumental variables have an F test value close to or less than 10, it should be considered as a weak instrument group according to a finger rule established by Staiger and Stock (1997). This was corrected by Stock and Yogo (2005), who simulated critical values to detect weak instruments under multiple endogenous explanatory variables using a Wald test based on the Cragg-Donald statistic.
In replicating the study by Parada-Contzen, Riquelme-Won, and Vasquez-Lavin (2013) with data from CASEN 2013, the value of the test proposed by Stock and Yogo (2005) is lower than the critical value, so the hypothesis of weak instruments cannot be rejected. In contrast, if the instruments used in the present study are considered, the values of the tests in the 2SLS and Heckit 2SLS models are much higher than the critical value, which is why the hypothesis of weak instruments is rejected in this case.
Regarding the exogeneity condition, only three of the instrumental variables proposed in this study fulfilled the Hansen J test, which evaluates partial exogeneity. These instrumental variables were the number of people who are economically dependent on the household, the proportion of large firms by economic sector and the proportion of small firms by economic sector. Consequently, the inclusion of these three instruments meets the requirements of relevance and exogeneity required by the method of instrumental variables; therefore, they were the only ones used in the regressions reported in Table 4. While replicating the study of Parada-Contzen, Riquelme-Won, and Vasquez-Lavin (2013) with the data from CASEN 2013, the value of the J test is high, rejecting the hypothesis of partial exogeneity of the instrumental variables included in that study.
|Coef.||St. Dev.||Coef.||St. Dev.||Coef.||St. Dev.||Coef.||St. Dev.|
|Test for weak instruments||2549.8||**||2546.8||**|
|Hansen J Test||0.516||1.152|
|p-value χ2 (1)||0.473||0.283|
From the tests performed, it is concluded that the instrumental variables used by Parada-Contzen, Riquelme-Won, and Vasquez-Lavin (2013) correspond to weak instruments and do not meet the requirement of exogeneity. Therefore, the parameters estimated through the 2SLS method based on these instruments would be biased and inconsistent, which would explain the high value of the VSL for Chile estimated by that study compared to other estimates for countries with similar GDPs per capita.8 In contrast, the three instrumental variables used in this study meet the relevance and exogeneity requirements, which validates the estimates made by the 2SLS and Heckit 2SLS methods. However, because we detected the presence of a selection bias (significant inverse Mills ratio variable in the Heckit regression), the best statistical model is Heckit 2SLS, which delivers a VSL of US$3.73 million (see Table 5).9
|IC 95% [higher – lower]||[0.70–1.57]||[0.69–1.55]||[3.49–4.07]||[3.44–4.02]|
|VSL (10th percentile)||0.30||0.30||1.02||1.00|
|IC 95% [higher – lower]||[0.19–0.42]||[0.19–0.42]||[0.94–1.09]||[0.92–1.08]|
|VSL (25th percentile)||0.61||0.60||2.03||2.00|
|IC 95% [higher – lower]||[0.38–0.84]||[0.37–0.83]||[1.87–2.19]||[1.85–2.16]|
|VSL (50th percentile)||0.76||0.75||2.54||2.50|
|IC 95% [higher – lower]||[0.47–1.05]||[0.46–1.04]||[2.34–2.73]||[2.31–2.70]|
|VSL (75th percentile)||1.21||1.20||4.06||4.01|
|IC 95% [higher – lower]||[0.75–1.69]||[0.74–1.67]||[3.75–4.37]||[3.70–4.32]|
|VSL (90th percentile)||2.12||2.11||7.11||7.01|
|IC 95% [higher – lower]||[1.32–2.95]||[1.30–2.91]||[6.56–7.65]||[6.47–7.56]|
Lindhjem et al. (2011) mention that it is not appropriate to compare estimates of the VSL obtained through different approaches. However, for illustrative purposes only, Table 6 presents previous estimates made in Chile using the declared preference approach.
|Stated preference approach||VSL estimated (millions of US$ 2013)|
|Ortúzar, Cifuentes & Williams (2000) – road safety||0.68|
|Ortúzar, Cifuentes & Williams (2000) – air pollution||0.41|
|Rizzi & Ortúzar (2003)||0.28|
|Iragüen & Ortúzar (2004)||0.39|
|Hojman, Ortúzar & Rizzi (2005) – road safety route 5||0.40|
|Hojman Ortúzar & Rizzi (2005) – road safety route 68||0.38|
|GreenLab UC (2014) – road safety||0.82|
|GreenLab UC (2014) – air pollution||5.40|
Most of all, the estimates obtained through the declared preference approach are several times smaller than those estimated through the revealed preference approach estimated in this study, which contradicts the results found by De Blaeij et al. (2003). The lowest VSLs were published in scientific journals, whereas the highest VSLs were estimated in a report by GreenLab (2014) developed for the Chilean Ministry of the Environment. In addition, it is observed that none of the estimates with stated preferences are found in the confidence intervals reported in Table 6.
In this section, the available estimates for performing a meta-analysis and extrapolating the VSL for different countries in Latin America are reviewed. For this, the results of previous studies that use the hedonic wage method published in scientific journals are used, including the estimated VSL for Chile in this research.
To determine the relationship between the GDP per capita and VSL for each country, linear and logarithmic regressions were estimated. The regression with the least mean square error was as follows:
Thus, equation (10) was used to generate the VSL extrapolations for the different countries of Latin America, using the GDP per capita from 2013 of each country reported by the World Bank (see Table 7).
|Country||GDP per capita (millions of US$)||VSL (millions of US$)|
|Australia (Miller, Mulvey & Norris 1997)||67.6||25.7|
|Canada (Lanoie, Pedro & Latour 1995)||52.3||26.6|
|Canada (Meng & Smith 1999)||52.3||9.6|
|Canada (Gunderson & Hyatt 2001)||52.3||27.2|
|Chile (Parada-Contzen, Riquelme-Won & Vasquez-Lavin 2013)||15.7||14.8|
|Chile (study under method Heckit 2SLS)||15.7||3.7|
|Germany (Schaffner & Spengler 2010)||46.4||9.3|
|Hong Kong (Siebert & Wei 1994)||38.4||2.4|
|Spain (Riera Font, Ripoll Penalva & Sbert 2007)||29.4||2.7|
|Switzerland (Baranzini & Ferro Luzzi 2001)||84.7||10.5|
|Taiwan (Liu & Hammitt 1999)||18.5||1.0|
|Turkey (Polat 2014)||11.2||0.2|
|UK (Siebert & Wei 1994)||42.3||28.1|
|UK (Arabsheibani & Marin 2000)||42.3||27.3|
|UK (Sandy & Elliot 1996)||42.3||42.2|
|UK (Sandy et al. 2001)||42.3||7.7|
|USA (Viscusi 2003)||53.0||18.0|
|USA (Viscusi 2004)||53.0||5.7|
|USA (Evans & Schaur 2010)||53.0||9.6|
|USA (Scotton & Taylor 2011)||53.0||12.4|
The results of Table 8 show that the estimated VSL for Chile from the meta-analysis is lower than the VSL estimated in this study using instrumental variables (2SLS or Heckit 2SLS). It could be explained because meta-analysis does not include many observations from developing countries. In consequence, the results show the importance of performing empirical studies with micro-data in each country to have more accurate estimates In addition, Chile has the third highest estimated VSL based on the meta-analysis approach, behind Puerto Rico and Uruguay, which have estimated VSLs of US$5.20 million and US$2.18 million, respectively. In contrast, the lowest VSL is presented by Haiti, which amounts to US$0.01 million, followed by Nicaragua, Honduras, and Bolivia, which have values of US$0.06 million, US$0.09 million, and US$0.12 million, respectively.
|Country||GDP per capita year 2013 (millions of US$)||Estimated VSL (millions of US$)|
The results of the meta-analysis carried out in this study provide evidence to suggest an income elasticity higher than 1.6, which agrees with recent studies that suggest the use of elasticities greater than 1, especially when results are extrapolated to low-income countries (Hammitt and Robinson 2011).
In this study, we obtain the value of a statistical life in Chile using labor market information under different estimation methods to later calculate the VSL for different countries of Latin America through a meta-analysis.
Estimates for Chile with labor market data at the individual level are approximately double the values obtained by extrapolating the VSL from other studies of hedonic wages for countries with a similar GDP per capita. This shows the importance of performing empirical studies in each country to have more accurate estimates. In particular, the Heckit 2SLS method presented a VSL value of US$3.73 million (between US$3.44 million and US$4.02 million with a 95 percent confidence interval). It should be noted that the use of instrumental variables with weak instrument tests and partial exogeneity was validated, so the estimated parameters should be consistent despite the endogeneity of explanatory variables associated with fatal and nonfatal risk.
Additionally, from the meta-analysis, the VSL is obtained for each Latin American country, with an average value of US$0.82 million for this region. In addition, it is concluded that before an increase of GDP per capita of 1 percent per year, the VSL would grow by 1.64 percent.
Despite the low amount of data available to perform the meta-analysis and the fact that the scarcity of studies for low- and middle-income countries limits the extrapolation of VSLs for Latin American countries, the results obtained in this study could be an acceptable proxy in relation to the value of statistical life, considering that there are many countries in Latin America that do not have their own VSL estimates and that this information would allow for better decision-making in projects that directly or indirectly involve changes in the mortality risk of people.
2In Chile, a small panel database at the individual level with labor market information is available only for the years 1996, 2000, and 2005 (CASEN Panel Survey), but for the same years, it is not possible to obtain official statistics on the risk disaggregated to the economic sector level.
3An instrumental variable is an exogenous variable that should not be included in the initial model (requirement of exogeneity) and must be partially correlated with the endogenous explanatory variable (relevancy requirement).
4Encuesta de Caracterización Socioeconómica Nacional, CASEN 2013 (Ministerio de Desarrollo Social, 2015), http://observatorio.ministeriodesarrollosocial.gob.cl/documentos/Metodologia_Diseno_Muestral_Casen_2013.pdf.
5Informe Nacional 2013: Estadísticas sobre seguridad y salud en el trabajo, August 2014, Gobierno de Chile, Superindendencia de Seguridad Social, http://info.suseso.cl/awp/publicaciones/informe_nacional_2013.pdf; Informe Final de la Comisión Asesora Presidencial para la Seguridad en el Trabajo 2010, http://datos.gob.cl/uploads/recursos/informeComisi%C3%B3nSeguridaddelTrabajo.pdf; Estadísticas de Accidentabilidad, versión 2011, 2012 y 2013, http://www.suseso.cl/608/w3-propertyvalue-59544.html.
7In replicating the previous study by Parada-Contzen, Riquelme-Won, and Vasquez-Lavin (2013) with the data from the CASEN 2013 survey, a VSL of up to US$16.6 million (estimates not reported by space themes) is obtained, similar to the value obtained by them (US$14.8 million, updated to 2013 dollars).
Cristian Mardones is associate professor at the Department of Industrial Engineering, University of Concepción. He received a PhD in economics from the University of Chile in 2009. He has been active in the areas of environmental economics and economic modeling for ten years, with publications in Environmental Impact Assessment Review, Energy Economics, Energy Policy, Journal of Technology Management and Innovation, Journal of Environmental Management, Economic Systems Research, Energy & Environment, Environment Development & Sustainability, Journal Economía Chilena, CEPAL Review, and Latin American Journal of Economics, among others. His professional experience includes consultancies for the Ministry of Environment in Chile. His current research involves studying the optimal level of pollution and economic effects of carbon taxes.
Marcelo Riquelme is master in industrial engineering from University of Concepción (Chile) in 2016.
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