Information, Marijuana and the Youth: evidence from French epidemiological data. Fabrice Etilé INRA-CORELA May 23, 2002 Abstract Using French epidemiological micro-data on the health and the lifestyle of teenagers in secondary schools, we measure the impact of a number of information providers on youth marijuana consumption. Information variables are instrumented so as to pick up the pure preventative e¤ects only, we control for habit formation and use of Heckman-Singer semi-parametric techniques allows us to control for unobserved heterogeneity, and to characterise the p opulation by latent classes. There are three latent classes, which represents 58, 23 and 19% of the sample. We use psychological variables and information on other risky behaviours to show that groups do not di¤er by their time preferences but rather by their risk aversions. A general conclusion is that information policies may have heterogeneous and counterproductive e¤ects. Further, we provide evidences that information a¤ects both the preferences and the risk perceptions, and thus has perhaps only transient e¤ects. J.E.L. Classi…cation : C24,D83,I12,I18 Keywords: Marijuana, Alcohol, Information. Acknowledgement 1 I have bene…tted from discussions with Andrew Clark, Patrick Peretti-Watel, Pierre Kopp. I thank seminar participants at OFDT/MILDT, INRA/CORELA, University of Paris 1/TEAM. I gratefully acknowledge research support for this paper from MILDT/INSERM, University of Paris-1/TEAM and INRA/CORELA. Usual disclaim applies. 1 “They say, and it is nearly true, that this substance does not cause any physical ill; or at least no grave one; but can one a¢rm that a man incapable of action and …t only for dreaming is really in good health, even when every part of him functions perfectly? Now we know human nature su¢ciently well to b e assured that a man who can with a spoonful of sweetmeat procure for himself incidentally all the treasures of heaven and of earth will never gain the thousandth part of them by working for them. Can you imagine to yourself a State of which all the citizens should be hashish drunkards?” Charles Baudelaire (1860) in “Arti…cial Paradises...On haschish and wine as means of expanding individuality” 1 Introduction Within less than a decade, marijuana use has increased dramatically among French teenagers. By 1993, annual prevalence among 17-year old male was 21%. Six years later, 47% of this gender-age class reported use in the past year [(13), (5)]. Marijuana use is associated with a number of physical and psychological damages such as increased risk of airways diseases, changes in motivation, cognitive impairments, tolerance e¤ects, withdrawal symptoms for chronic heavy smokers, and perhaps gateway e¤ect [(40), (31), (32), (26), (15), (47), (45), (50)]. Non-medical use of cannabis does not only generate social costs (through increasing utilization of medical services for example, [(40), (11), (47), (45), (33)])1 , it could also give rise to well-being losses for the consumer. This is the case when she is not perfectly informed of the e¤ects of consumption on her future preferences (through habit formation and changes in health capital)2 . Some recent works emphasize the impact of risks perception and social “climat” on trends in the prevalence of marijuana use in the U.S.A. [(2), (45)]. In light of this result, information as well as price could be an e¢cient regulatory tool. Understanding the e¤ects of information on youth marijuana consumption may allow us to develop preventative strategies to reduce consumption3 . The French drug regulation agency (MILDT) has designed its policies on the assumption that information will impact drug consumption e¢ciently. However, 1 Social costs generated by cannabis consumption are qualitatively similar to those of any illegal drug: accidents, cardio-vascular and cancerous morbidity, tra¢c-related violence. In France, some rough estimates of these costs shows that they are greatly inferior to those of le gal drugs [ (33)]. However, they should sharply increase with the ageing of the former users’ population. 2 This is also the case if she is inconsistent i.e. if she does not do what she planned to do even though her environment remains stable. This kind of behaviour can be rationalized by assuming non-stable preferences or hyperbolic discounting. It is always possible to tax addictive products in such a way that hyperbolic discounters choices are those of exponential discounte rs facing the true market prices. [(24)]. 3 Usual variables to regulate addictive consumptions such as excise taxes, spatial, temporal or age-based selling/consumption restrictions are likely to be useless for cannabis. Sparse estimates yield negative price elasticities ofdemand for marijuana [(41),(44), (10)]. As price data are rarely available, previous studies have been interested in the e¤ect of the full price of marijuana. Most studies …nd that the legal risks are negatively correlated with prevalence [ (37), (49), (48), (44), (16)]. However, the teenagers seem to be less responsive to higher …nes than young adults [(12), (21)]. 2 in reality the diversity of information providers “may limit the e¤ectiveness of a well-designed policy initiative, as prevention information for adolescents may appear confused, is likely not to be believed, and is thus ine¢cient”. [(36)]. This paper therefore adress the following issue: what type of information provision will be the most e¢cient for a public health campaign aimed at marijuana? I use a French epidemiological database about health and lifestyles of highschool teenagers, in which information variables are as following : “has had or followed discussions about drugs within your family, your school, with your friends and/or in the medias” (several choices allowed). With these variables, we can neither be more precise about the content of the provided information, nor can we be more speci…c about the way a youth understand information and use it to revise their beliefs. Moreover, as we have cross-section data, the information variables may be endogeneous or determined simultaneously with consumption. Accordingly, I only identify the e¤ect of information providers on marijuana annual prevalence among the youth, and the variables are always instrumented. Risks perception and responses to information providers may be very heterogeneous [(45)], and we would like to identify those individuals who are sensitive to public information campaigns. Furthermore, the dynamic of consumption may vary according to past consumption history and other idiosyncratic factors. I therefore control for past use and unobservable heterogeneities in our estimates. This has led me to use the Heckman-Singer semiparametric technique, which allows to classify individuals in groups (or types/classes) whose risky behaviours and reactions to information are clearly di¤erentiated. Besides, it should also be borne in mind that alcohol use is deeply rooted in French customs and recent research suggest that strong interdependancies between alcohol and marijuana consumption are of major importance in the design of public policy [??, ??]. In an attempt to control for the e¤ects of alcohol regulation and to identify more accurately teenagers’ typical behaviours, I estimate together equations for marijuana participation in the past year, heavy drinking (drunkenness in the data) in the past year and the age of initiation into cannabis or heavy drinking, and also use information variables relating to alcohol4 . To anticipate the main result, I …nd that the population can optimally be described by three latent classes, which represents respectively 58, 23 and 19% of the sample. These types are featured by di¤erent propensities to consume alcohol and marijuana, and by di¤erent reactions to information. These pieces of statistical evidence point to the importance of accounting for unobservable heterogeneities when evaluating drug policies. The paper is laid out as follows. In the following section, we brie‡y review the 4 We were unable to identify the main parameters of the structural model proposed by DiNardo and Lemieux (2001) for three reasons : (i) there are too few teenagers (only 3.8%) having smoked marijuana without having been drunk in the past year ; (ii) we work on microdata and not state-level agreggated data ; (iii) we have any regional price variables which help identify this model. In line with argument (i), we have assumed that contemporaneous correlations between heavy drinking and marijuana use are captured by the unobservable heterogeneities. 3 theoretical literature on information and addiction. The third section describe the data, and emphasize the role of unobservable heterogeneities and career (or habit formation) e¤ects. Section 4 presents the empirical model and section 5 contains our results. I show that the observed consumption behaviours are a probabilistic mixture of well de…ned “pure” types. In section 6, I interpret the results using some additional estimates. I conclude on the e¢ciency of the current French policy. 2 2.1 Theoretical analysis Information, rational addiction and the full price of consumption In Becker and Murphy’s rational addiction model, the current consumption is explained by past consumption history, the market prices, and the current and future costs arising from consumption through anticipated habit formation and destructions of human capital. The agent chooses to consume a quantity that equalizes the current marginal utility of consumption and its full price. Due to a lack of price data, a majority of empirical studies on cannabis highlight other components of this full price such as : (i) the legal risk (ii) the short and long term health risks and (iii) the risk of stigmatization. Following Bachman and al. (1998), Pacula and al. (2001) provides some strong evidences of the e¤ect of risk perceptions. Using panel data analysis, they …nd that changes in perceptions and attitudes, which are captured by a qualitative judgement index, contributed for 50% up to 80% to changes in the US agreggated marijuana consumption by high school seniors between 1982 and 1998. Orphanidès and Zervos (1995) gained a new insight into the modelization of addiction behaviour, by assuming that information is not perfect. If the risk of addiction is not known with certainty before initiation, informations about the side e¤ects of recurrent intoxications become of a great importance. Individuals may be interested in gathering informations about the frequency and the magnitude of risks. In a recent study, Clark and Etilé (2002) …nd that most of the past health changes of smokers or other smokers in the same household are positively correlated with smoking. This may re‡ect the presence of adaptive behaviors using health changes as information. Last, information modi…es also the perception of the consumption bene…ts as sketched in Duesenberry (1949). In harmony with these theoretical and empirical insights, the participation decision can be formalized very simply. Let Ui be the current well-being of the agent i, net of any current consumption cost. It is a function of a composite aggregate y i, the quantity of cannabis consumed, x i, and the level of habit formation h i. Uncertainty about the taste for a drug experience is summarized by r~i .We assume that young people cannot access the credit market. The full price ¦i is a function of the market price p, the past, current and anticipated career of consumption hi ,and the future costs ci which depends on a risk ~¼ i. If E(.) is the expectation operator, we observe participation conditionally to the 4 information set when : ¯ © ª¯ @E fUi(yi ; x i; h i; r~i )g ¯¯ > E ¦i(p; ci(h i; ¼~ i ) ¯x =0 ¯ i @x xi=0 (1) Information may impact the probability of participation through changes in anticipations relating to r~i , ¼~ i , and ci(:). Moreover, in a brilliant ethnographical study, Howard Becker (1955) showed that information and learning processes are the catalysts of involvment in drugs, as the drug market is a black market and the e¤ects of drugs are likely to be unknown a priori and idiosyncratic. Information may change directly either the full price of the consumption (perception of the risk ~¼ i) or the instantaneous preferences (perception of the taste parameter ~ri), and it will have an indirect cumulative e¤ect through rational anticipation of habit formation. In the current paper, I do not study the dynamic of beliefs revision and consumption, as the data set is cross-sectional, but rather the heterogeneity of the reactions to the contacts with several information providers. For the same reason, I do not control for future consumption, as required by the rational addiction theory, but only for past consumption (anticipations are thus adaptive). It is shown in section 6 that information generally a¤ects participation through changes in full prices and instantaneous preferences. 2.2 Prevention policies and the heterogeneity of information e¤ects I investigate neither the information search behaviours of the teenagers 5 nor the changes in consumers’ attitudes and awareness toward health or addiction.I focus rather on the preventative e¤ects of information in order to evaluate the e¢ciency of information-based policies These prevention policies aim on one side at diminushing the probability of consumption (primary prevention) and, on the other side, at reducing the health risks generated by consumption (secondary prevention). We have some good reasons to think that prevention may have unexpected e¤ects. Indeed, suppose that an information provider plays the role of a “forecasting center” for a teenager who is not certain of the outcome of a drug experience. This provider send the following signal: “if you take drugs, it will bring you a net bene…t x”. The teenager uses this forecast as the virtual outcome of her/his experience if and only if she/he trusts the provider. Hence, this virtual outcome, weighted by the provider’s credibility, is processed as a virtual experience and helps forming expectations about the real outcome of the experience. If she/he decides to consume, she/he will compare this latter to x. Then, if the provider’s forecast has been misleading, she/he will revise her trust in this 5 Information may have been gathered after a search. The ex-ante demand for information depends on the search cost and the expectation of the e¤ects of information on future decisions and well-being [(27)]. The more there is uncertainty, the more the consumer nee ds information to reduce it. 5 provider, whose credibility will fall. The more she/he has experimented drugs, the lower the credibility of the provider will be if its forecasts are always wrong. If she/he is bayesian and assuming that the signal is discrete6 , informations that do not sound credible may have the opposite e¤ect to what was expected 7 . Preventative information toward teenagers usually underscores only the damages generated by drug consumption (the health risks). But the …rst experiences are usually the best. If consumers’ anticipations are adaptive and not rational, the good outcomes of the …rst experiences will shift downwards the anticipated future costs of consumption. The youths discount also heavily the future costs of current consumption as their time preferences are more myopic (and time preferences may be shifted endogeneously by drug consumption, see [(7)] and [(43)]). Further, they may value risk-taking behaviors di¤erently. If the anticipations of well-being proposed by an information provider are never consistent with the subjective well-being felt by the teenagers, these latter will rationally choose to act in opposition to the messages. Juvenile behaviors are often explained by a will of infringing some taboos, but considering more carefully the way individuals process information may also help to rationalize these “deviances”. In the end, unobervables heterogeneities related inter alia to the subjective discount rate and risk aversion generate interpersonal di¤erences in the perceptions and uses of information. There are also some variations in the way agents process information, as the gap between the perfect bayesian rationality and the “practical rationality” (Bourdieu, 1972) implemented by agents is not negligible. In a nutshell, the variables capturing contacts with information providers may have heterogeneous e¤ects, insofar as we do not observe the beliefs revision process. 3 3.1 The data The epidemiological data set INSERM 1993 The current paper exploits French epidemiological data from a 1993’s survey conducted by the French National Institute of Medical Research (INSERM - unit n ± 472). The national sample of 12931 teenagers is representative of scholars enrolled in secondary schools. Those in their …rst two years of secondary school (about 4000 8 ) did not have to reveal their current drug consumptions. Note also that (i) going to school before 16 is an obligation in France and (ii) some of the teenagers in the sample are aged over 21. The analysis exclude these latter, as they may present speci…c caracteristics (scholars usually achieve their A-levels 6 Like “you ought not to take drugs because you will get into trouble” or “take drugs, it will be marvelous”. 7 This should not hold anymore if the signal is continuous. 8 About 85% of these 4000 te enagers are aged under 13. As drug-taking behaviours and school outcomes or drop-outs may be correlated, the remaining 15% and those who left school after 16 might have had an higher probability of drug use. We can not correct this selection bias. 6 by 18-year old). Extensive statistics and some notes of methodology may be found in [(13)]. Some descriptive statistics are also reported in annex A. The fear of being stigmatized as deviant (cannabis consumption is illegal in France) or of presenting a bad image of one’s community9 [(29), (1)] and retrospective questions about the age of initiation and lifetime consumption can yield measurement errors. However, there are few abnormal answers and few missing values for the variables describing cannabis or alcohol consumption (between 4 and 10% for alcohol, and less than 6% for cannabis), which suggests that the teenagers answered sincerely. 3.2 Cannabis consumption and heavy drinking: some evidences Grouped count variables give information about the consumptions of several drugs: cannabis, glue/solvent, pharmaceutical drugs, heroin, cocain, hallucinogens or amphetamins consumed up to 2 times, between 3 and 9 times or more than 10 times in the life and the last 12 months. Frequencies of participation are very low, except for cannabis: 85% of the youths had never smoked cannabis in 1993. 9% had done it between 1 and 9 times, and 6% more than 10 times 10 . It is not possible to distinguish in the data chronic users from occasional ones. Moreover, youths may likely underestimate their consumption in order not to be stigmatized as addicts. I will thus focus on the participation decision. By using the age of initiation and the age of the individual at time of the survey, we can bound the duration since initiation in a two-years interval11 . 83% of the teenagers who had been initiated since more than one year took drugs during the last 12 month. The distribution of consumption in the past year, as a function of a proxy for time elapsed since initiation (age-age of initiation) indicates that there are two groups: on one hand regular users and on the other hand quitters and casual users (cf. graphic 1). The proportion of regular users (more than ten times during the last 12 months) seems to be positively correlated with duration since …rst use. This stylized fact gives rise to two interpretations. First, duration since initiation could be a proxy for habit formation e¤ects (cf. section 2), if we assume that use has been continuous since initiation. We ought to distinguish regular smokers from the youths having had few experiences since their initiation. The trend e¤ects generated by habit formation will di¤er 9 Ethnical minorities are not yet institutionalized in France and, at the time of the survey, urban areas were not yet segregated on an ethnical basis but rather on a …nancial one. However, the youth originated from immigration, which lives in poor suburban areas often regard themselves as elements of a speci…c social group. 1 0 Straight comparison with a similar survey of 1999 shows that in 6 years the abstinence rate fell by 20%! 1 1 ]age-age of initiation-1;age-age of initiation+1]. Lifetime consumption includes occsions of consumptions in the past year. We know the year and month of birth, the year and month of the survey but just the year of initiation into cannabis and heavy drinking. 7 100% 80% More than 10 60% Between 3 and 9 1 or 2 40% Abstinence 20% 0% 0 1 2 3 4 5 6 Time elapsed since initiation Figure 1: Consumption in the past year vs. mean duration since initiation in magnitude according to this unobservable heterogeneity. Nevertheless, ceteris paribus, the earlier the initiation occurs, the higher the participation probability seems to be. However, once again, partially observable heterogeneities or a third factor (such as the marital status of the parents, family dysfunctions or poverty) could explain both the precocity of involvment in drugs and the intensity of lifetime consumption. As the sample does not include youths that had ended up their studies in secondary school, it is not possible to test correctly one explanation against the other. In some preliminary estimates, we found that, after controlling for age, the age of initiation is not correlated with the participation probability, by contrast with the duration since initiation. Thereby, I use this latter as a proxy for habit formation and control for the unobservable heterogeneities generated by the diversity of individual careers. Besides, epidemiological researchs show that there is a progression in drug involvment, from cigarette and alcohol to marijuana and sometimes other drugs [??, ??]. Whether this progression is explained by sociological factors (cf. the learning theory proposed by Howard Becker), pharmacological ones, or a third factor is beyond the scope of this paper. What really matters is that adolescents are very unlikely to experiment with marijuana without prior experiences with alcohol. Consequently, unobservable heterogeneities that explain cannabis consumption should also carry weight in alcohol participation. It is well-known that wine drinking is deeply rooted in French culture. Alcohol (and often binge) drinking is not considered as an unhealthy activity as it is in North America, so that it would be a nonsense from a comprehensive point of view, to compare alcohol and cannabis consumption1 2 . Accordingly, I 1 2 France is the country where the average alcohol consumption per inhabitant has decreased 8 have rather considered the life and yearly numbers of heavy drinking occasions (in the data, drunkenness which is also a grouped count data variable), as well as the age of initiation to drunkenness. drunkennesses are positively correlated with usual drinking behaviour. 97.8% of the cannabis-initiated youths had still drunk alcohol and 89.2% had still been drunk. Furthermore, past-year cannabis consumption and drunkenness occasions are highly correlated. Whilst 96% of those who were not drunk did not smoke cannabis, 70% of those who were drunk more than ten times did it. The assumption of independance between both variables is rejected by a  2 test1 3 . Otherwise, only 3.8% of the youths took drugs and were not drunk in the past year14 . These …gures imply that we can not analyze cannabis consumption without accounting for heavy drinking. This reason has led me to use informations about heavy drinking and the age of …rst alcoholic/mariholic drunkenness in order to identify the unobservable heterogeneities (cf. section 4). To be consistent, I use information variables related to alcohol as explanative variables. 3.3 Information variables The information variables are labelled as following : “has had or followed discussions about drugs/alcohol within your family/at school/ with your friends/in the medias” (several choices allowed, 8 variables). Hence, we know the identity of some information providers but not the content of the informational signal. We expect a priori that parents talk their children out of taking drugs. But some adults may be very liberal if, by instance, they are themselves current or former drug-users. Furthermore, lifetime cannabis use is negatively correlated with variables that capture the quality of the relationship between the children and their parents15 . The absence of discussion about drugs within the family may therefore be correlated with cannabis use through a third factor, namely family dysfunctions. Many parents begin to talk about drugs with their children after having found out that she/he takes drugs. Likewise, until 1990/1996 the ma jority of schools used to set up information-based preventative campaigns after the police had to intervene against a tra¢c. Note also that young drug users may be more involved in seeking informations about drugs in the medias. However, the French teen press has always been quite hostile to drugs. the most, going from 17.7 litres of pure alcohol in 1961 to 10.7 litres in 1999. However, in 1996, the average consumption in France was 11.2 litres, to be compard to 7.9 in the UK, 6.6 in the U.S.A. and 6.2 in Canada. Note also that a simple glass of alc ohol does not provide the same rapture as heavy drinking and cannabis smoking do. ni: n:j 2 ) 1 3 The test statistic is: d2 = P P (nij¡ n ni:n:j 1 4 Note n that these youth do not have particular ethnical caracteristics such as being originated from North-Africa or Middle East. 1 5 Thre e questions labelled as follows: “Family life is to your opinion, rather tense (y/n), pleasant (y/n), to be sought after (y/n)”. And one question about the sujective feeling of having thoughtful parents: “My parents are interested in what I do/ would be interested if they had time for/ take too much interest in what I do/have little interest in what I do”. 9 Friends are costless information providers. 78% of cannabis users still talked about drugs with their friends, whereas it is the case for only 48% of nonusers. But information gathered by observation or cheap-talk, or the will to get a status among one’s peers can generate herd behaviour [(9), (19), (4)]. The identi…cation of the e¤ect of peer information requires some instruments in order to control for the re‡ection e¤ect [(34)]. Where did friends get their information? If they are themselves consumers, they will tend to justify their consumption to their friends. Last, some common caracteristics (the socio-economic status of the parents, the ethnical origin, the living area and a number of other environmental factors) may explain both the formation of a peer group and the decision of its member to consume or not. As information variables are likely to be endogeneous, I instrument them. 3.4 Income, prices and other variables Occasionnal cannabis users often consume for free as the drug is bought by those of the peers who are regular smokers[(30), (1)]. The market price may thus have little e¤ect on the probability of participation. Otherwise, the price of a “standard” quantity of cannabis is constant since 20 years, whereas weight and quality of this unit can vary according to the place and the moment of the transaction (about 15 euros for 2 to 4 grammas16 ). There were no centralized and regional statistics of drug-related crimes until the early nineties, even though the enforcement of drug laws varies across the areas of jurisdiction. I just build from the data an indicator for the avalaibility of cannabis. It is the rate of young scholars initiated into cannabis and attending school in the same o¢cial educational area and living in the same kind of area (town or country)1 7 . Due to network e¤ects and stigmatization, it is less costly to buy and consume cannabis where there are more users. This variable may be endogeneous as there are not many observations in some of the geographical cells. The rate of users varies from 9% up to 18% percent for a population of 188 up to 1395 youngs. There is at least 24 initiated youths per cell. I build a similar indicator for drunkennesses. While estimating the empirical model, I have noticed that introducing these variables meliorate the identi…cation of the heterogeneities. Regional prices of alcohol are not available. Moreover the administrative (and economic) areas of residence are not in our data. However, I use in section 6 the price of alcohol to estimate duration models for the age of cannabis initiation. It is the yearly price index of alcoholic beverages de‡ated with the consumer price index (base 100 in 1980, INSEE price indices). This index is not quite appropriate as a representative youth consume more beer and less wine than a representative French household. Their average shopping basket is also di¤erent. Few French youths have a job. Hence, their income consists mainly of the pocket money given by their parents, which is known. Otherwise, I used dum1 6 The main quality sold in France is the haschisch from Morocco, which is often blended with para¢na, a kin of haircare powder called henné, and residuals from tyres. 1 7 More precisely, it is the number of the initiated youths who were surveyed before {age of initiation+1} as we do not know precisely the date of initiation. 10 mies for pubescence (to control for biological changes) and gender. 4 4.1 Empirical modelling Basic speci…cation The main dependent variable is CANyr : “Did you consume cannabis during ¤ the last 12 months”. Let YiC be a latent variable for the past-year cannabis participation decision of agent i. The observed dependent binary variable is Y iC , which is equal to 1 if the teenager consumed, and 0 otherwise. Let XiC be a vector of explanative variables, the probit model reads : ½ ¤ 0 if YiC = XiC ¯ C + ~º iC < 0 Y iC = (2) ¤ 1 if YiC = XiC ¯ C + ~º iC > 0 and its likelihood is : LC (Y iC jXiC ) = [1 ¡ ©(XiC ¯ C )]1¡Y iC [©(XiC ¯ C )]YiC (3) where © is the cumulative of the standard normal law. 4.2 Heterogeneity We know that unobservable heterogeneities can bias the correlation inferred between past use history (captured by trend variables) or the way information is processed and consumption. A common antidote to the omission of possibly unobservable variables is to model the unoberved heterogeneity as individualspeci…c random e¤ects. But inference can be sensitive to the assumed distribution of the unobserved heterogeneities. An alternative way to deal with this problem, is the semi-parametric estimator of Heckman et Singer (1984). Assume that the population consists of a possibly unknown number S of subpopulations (or components/classes/types). Some decision parameters may vary from one class to another. Hence, the coe¢cients ¯ C of the covariates vary across the sample according to some distribution, which is supposed to be discrete. As the component membership is not known, the likelihood of observation i is a mixture of the probability densities of this observation, when sampled from components s = 1; :::; S. All observations have the same unconditionnal probability ®s to belong to the latent class s = 1; :::S. . We have therefore to condition the individual likelihood by ®s . The likelihood of the sample becomes : " S # N Y X L= ® s LC j s(Y iC jXiC ) (4) i=1 s=1 where : LC j s (Y iC jXiC ) = [1 ¡ ©(XiC ¯ C s )] 11 1¡YiC [©(XiC ¯ C s )]YiC (5) Using this …nite mixture model, we can interpret the point masses of the distribution of the coe¢cients as latent classes. Each class is representative of a type of consumption behaviour, and a type of reaction to information. Furthermore, unobservable heterogeneities should not change a lot along time. We thus have to incorporate other informations about past and current behaviours of the youths in order to identify more accurately the latent classes. Otherwise, they would capture the unobservable heterogeneities that are solely correlated with cannabis use in the past year. To circumvent this problem, I model cannabis participation together with heavy drinking in the past year (ALCyr)18 and the age of …rst cannabis use or …rst drunkenness (AGEmin). Hence, the latent classes that I will …nd out will not just mimic the observed classi…cation between users and non-users. As the empirical hazard function of initiation is not monotonous, I assume that AGEmin follows a loglogistic law (cf. the graphic in annex A). However, some individuals will never be alcohol or haschisch drunkards, and we should thus use a split-population duration model [(17)]. We can not identify properly such a model, insofar as we do not observe youths on the whole period at risk for initiation (from the age of 10 up to about 30). Note T i min the variable AGEmin, and ± i min an indicator which values 1 if the teenager has yet been initiated (and 0 by default). XiD is a vector of explanative variables. The likelihood reads for this model : LD (T i minjXiD ) = [S(T i min jXiD )]1¡±i min [f (Ti minjXiD )]±i min (6) where S et f are respectively the loglogistic survival and density functions. Last, ALCyr is modelled through a probit speci…cation. The likelihood is : LA (Y iAjXiA) = [1 ¡ ©(XiA ¯ iA )] 1¡YiA [©(XiA¯ iA )]YiA (7) Conditionning each likelihood by the latent class, we get the following full likelihood : 8 93 2 N S < = Y X Y 4 L= ®s LD j s(T i minjXiD ) Lj j s (Y ij jXij ) 5 (8) : ; i=1 s=1 j= A;C It is estimated by an E-M algorithm following Dempster and al. (1977). To …nd out the optimal number of classes, I just compare the …nal likelihood penalized by an ad hoc function, for the estimates of the model with 2, 3 or 4 classes. All parameters vary between latent classes, so that adding one class may 1 8 We were unable to identify the semiparametric bivariate probit model for cannabis use and heavy drinking, as one of the alternative (smoking and no heavy drinking) is rarely chosen. Indeed, in the maximisation step of the EM algorithm, we have to estimate equations for each class, by weighting individual contributions to the overall likelihood with the individual probability of belonging to the class. The choice smoking/no drinking may thus be undersampled...Hence, we implicitely assume that any contemporaneous correlation between both decisions is picked up by the mixture distribution of the constant in each equation. 12 be costly and useless 19 . To ensure the reproducibility of the results, I choose initial values by a two-step procedure 20 . First, I separate the sample in S groups using a cluster analysis, on the basis of several psychological variables (selfesteem, optimism, suicidal thougts, impatience, inconsistency). These variables might capture variations in the pure discount rate, that is the capability to make plans for the future and to follow them (Masson, 1995). In a second step, I estimate a multinomial logit for the probabilities of belonging to one or another group resulting from the …rst step. This logit was conditionned by the explanative variables of the model. Then, starting values for the E-M algorithm were set at the predicted probabilities of belonging. 4.3 Identi…cation Following Etilé (2002), I use the socioeconomic status (SES) of both parents to instrument the information variables. A simple probit analysis shows that father’s SES is not correlated with past year use, whereas mother’s SES generally is. The instrument set also includes dummies for the number of brothers and sisters, the marital status of the parents, the geographical localization (educational area and type of area: country/suburbs/center), the ethnicity, and some diseases (asthma, allergy, physical disability). Using bivariate probit regressions, I instrument simultaneously informations about alcohol and cannabis obtained from a same provider. I then introduce the predicted values of the probabilities of having had information in participation equations for drunkenness and cannabis 21 . According to the main predictions of the Economic of the Family, family information should be well instrumented2 2 . This is curiously not the case (cf. table A2 in annex A). Instrumentation does not solve the problem of contextual and correlated e¤ects2 3 , as parental SES may explain both the composi1 9 There is no test of the optimal number of classes as 0 is at the boundary of parameter space. Following Baker & Melino (2000), we use the following criterion : ln(L) ¡p ¤ ln(ln(N) where L is the …nal likelihood, p is the total number of parameters and N is the sample size . 2 0 The iterative Expected-Maximisation algorithm is monotoneously convergent, but it is possible to reach di¤erent maxima depending on the starting values. I tried several starting values and …nd that it converges toward the same maximum, at a slower speed than it did with predetermined starting values. 2 1 Assuming that there is no unobservable heterogeneity, usual methods for dealing with the endogeneity of information variables use the Heckman’s approach (as advocated by Vella, 1993): the model should be estimated from equations augmented with Mills ratios estimated from bivariate probit regressions (see for an example , Variyam and al., 1999). I did not investigate the compatibility of this approach and the Heckman and Singer’s te chnique. Moreover, in any two-step procedure, the variance of the coe¢cients of the instrumented variables are biased (Murphy and Topel, 1985). We have not yet corrected for these bias, and therefore the variances are probably downward biased. I will try to solve these problems in a future revision of this paper. 2 2 As there is a the trade-o¤ between quality and quantity of children, the preventative e¤ort should decrease with the number of children and increase with parental socioeconomic status. 2 3 Manski (1995, p.127) gives the following de…nitions of the three hypotheses which can explain the similarity of behaviours in a group : 1. “endogenous e¤ect, wherein the propensity of an individual to behave in some way varies with the prevalence of that behavior in the group.” 13 tion of the peer group, the quality of scho ol drug prevention programs and the propensity to take drugs. I should therefore control for parental SES in our main equations. However, the Heckman-Singer technique allows to use these variables as instruments only. The correlations between the instrumented information variables and past-year participation may therefore be interpreted as the measures of the primary preventative e¤ect of contacts with information providers. Last, note that identi…cation relies also on the non-linearity of the probit of instrumentation. 5 Results Results are reported in the tables 1 to 3 of annex B. In the probit equations, a …rst group of variables controls for trend e¤ects (or habit formation) generated by past uses of alcohol and cannabis. These variables are DURCAN et DURALC, which are built as the age at the time of the survey minus the age at the time of initiation into cannabis or drunkenness. When the teenager has never tried cannabis or heavy drinking, these variables are set at 0. When they value 1, I recode them at 0, as initiation may have occured during the last 12 months (cf. section 3.2). A second group of variables comes to control for gender, age, puberty and income. Last, a third group helps to identify the e¤ect of the full price: availability of cannabis on the one hand; informations about cannabis and alcohol on the other hand. Explanative and dependent variables are described in tables A1 of annex A. Explanative variables for the duration equation are dummies for generation e¤ects, gender, and a dummy which indicates if the natural parents lives still together2 4 . 5.1 A behavioral typology based on latent classes Individual heterogeneities are captured by 3 types, which represent respectively 58, 23 and 19% of the population. Given these estimates, we can use Bayes rule 2. “contextual e¤ect, wherein the propensity of an individual to behave in some way varies with the distribution of background characteristics in the group.” 3. “correlated e¤ect, wherein individuals in the same group tend to behave similarly because they face similar institutional environments or have similar individual characteristics.” 2 4 For a better inference, AGEmin is recoded as following : AGEmin = age at the time of the survey- 9 if the teenager has not yet been initiated into c annabis or drunkeness; AGEmin = (age at the time of the survey + age of initiation)/2 - 9 if the teenager has yet been initiated and age of initiation is equal to the whole value of the age at the time of the survey; AGEmin = (age of initiation + 0.5) - 9 if the teenager has yet bee n initiated and this age of initiation is equal to the whole value of the age at the time of the survey. Hence, I eliminate from the estimation sample individuals aged under 9. I could have adress the imprecision of our duration data by using a duration model, in which the second term of the likelihood, f (Ti min jXiD ), would be replaced by (S(Ti¤ jXiD ) ¡ S(min(Ti¤ + 1; T i )jXiD )), where Ti¤ is the age of initiation and T i the age at the time of the survey. Preliminary estimates have shown that this model does not yield di¤erent results and takes much more time to be estimated than our simpler speci…cation. 14 to calculate for each observation i the probabilities of belonging to classes 1, 2, or 3: Pr (i 2 sjY = ; Y iA ; T i min; X iC ; X iA; X iD ) Pr (Y iC ; Y iA ; T i min ji 2 s; X iC ; X iA ; X iD ) Pr(i 2 s) (9) PS s=1 Pr (Y iC ; Y iA; T i min ji 2 s; X iC ; X iA; X iD ) Pr (i 2 s) iC The probability in the numerator is the likelihood of observation i, conditionnal to being of type s. Furthermore, we know the mean caracteristics of an agent who would belong to one class s. The sample mean ex-post probability of belonging to the class s for agent i with caracteristic xi = 1 is given by : X 1 Pr (i 2 sjxi = 1) = Pr (i 2 sjY iC ; Y iA ; T i min; X iC ; X iA ; X iD ) #fi=x i= 1g i=xi =1 (10) Conversely, the sample mean type-conditional probability that x i = 1 is : 1 X Pr (i 2 sjY iC ; Y iA ; T i min; X iC ; X iA; X iD ) Pr(xi = 1ji 2 s) = xi (11) N i ®s Using other variables of risky behaviours, health status and socioeconomic caracteristics help to caracterize the behavioral features of each latent class. Some of the descriptive statistics I have computed for this analysis are presented in the tables of annex A. Youths of the …rst type25 are close to the pure type “abstinent”. Actually, 41% of them have still experienced tobacco whereas they are 64% and 80% in the two other classes. Less than 10% smokes at least one cigarette per day. Heavy drinking is rare. While 69% had still drinked alcohol, only 10% had still been drunk, and 2.3% had still used marijuana. Individuals from classes 2 and 3 di¤er essentially with respect to their drinking behavior. The mean age does not vary across classes (between 16 and 16.5) but those from the third type drink much more, with a rate of yearly drunkenness higher than 80%, whilst it is only 4.3% in the …rst class and 40.7% in the second. However, both second and third components have an high proportion of cannabis users, around 30%. The rate of risky consumptions (more than 10 marijuana uses or drunkennesses during last year) is also the same. But conversely, youths with risky consumption behaviours have a 50% probability of belonging to class 2, whilst it is only 30% for class 3. Last, the circumstances surrounding heavy drinking occasions are not the same across these two groups. Youths who drink more during family celebrations or with friends tend to belong to the third group. At the opposite, the teenagers who drink more when they are in a bad mood have an higher probability to belong to the second group. Thus, individuals who have non-social or dangerous uses of alcohol and marijuana are more likely to be of the second type, which could be caracterized as a “risky user” type, whereas the third type represents broadly “happy users” 26 . 2 5 In reality, a youth does not belong entirely to one class: this is an abuse of language as we consider indeed statistical entities not individuals. 2 6 This may re‡ect, of course, an european point of view wherein the lack of social and 15 5.2 Types, time preferences and risk aversion Do types di¤er with respect to their time preferences and risk aversion? If it were true, given that these factors are good predictors of risky behaviours, then probabilities of belonging should also predict these behaviours. Actually, youths from the second type tend to have more often sexual intercourses without preservatives and with di¤erent parters. Likewise, the conditional probabilities to have a sport or a road accident increase with the type. Last, a youth from the second and the third type get more pocket money (with a mean of about 31 euros/month to be compared to 22 euros for the …rst type), and we know that absolute risk aversion decrease with wealth. Hence, the second and the third type should be less risk-adverse. Preference for the future is said to be positively correlated with human capital and wealth, and negatively related to the psychological health status and lifecycle negative shocks [(35), (7)]. There are little di¤erences in the parental socio-economic status between types. Teenagers whose mother is blue or white collars have an higher probability of belonging to classe 2 or 3, whereas teenagers whose mother is at home or father is a worker tend to belong to class 1. School satisfaction and outcomes are about the same across all classes. I eventually use several questions bringing on the psychological pro…le and the lifecycle shocks of the teenager. These variables indicate if she/he is impatient, has lost heart, depressed or able to achieve the tasks she planned to do (which is a good proxy for dynamically inconsistent behaviours), and the marital status of her parents. They summarize the capability to make projects for the future (thus re‡ecting an high preference for the future, (35)) or shocks on the discount rate. Types 2 and 3 are more impatient and depressed, and less consistent. But variations of time preferences might be caused by consumption. Being depressed or impatient does not seem to be correlated with the probability of belonging to classes at odds for consumption. Conversely, having separated or deceased parents increases this probability. In the end, the link between types and the time preferences is fuzzy. As emphasized by sociologists [??], di¤erences in risk aversion play a more important role: in the referential of the teenage subcultures, risky behaviours often generate bene…ts that one can not ignore. Failure to take this into account may lead to overstate di¤erences in the time preferences across agents. 6 6.1 Interpreting the results Assessing the impact of information providers At …rst glance, an information provider will have a preventative e¤ect if it decreases the propensity to consume cannabis. But, as there are unobservable heterogeneities (cf. section 2.2), the results reveal a sharp distinction in the time boudaries around drug experiences rather than the level of consumption is seen as the main symptom of a true addiction. From a sociological point of view, the medical norms for addiction are not objective, but a cultural product of each society. 16 e¤ect of information providers, according to the group. Then, it might be thought that individuals use the same pieces of objective informations in many various ways. According to theory (equation 1 and DiNardo and Lemieux, 2001), information a¤ects participation probabilities by two channels, which consist of : ² modifying instantaneous utility (i.e. taste perception). Remember that trend variables control for any indirect lagged e¤ect through habit formation. ² changing the full prices (i.e. risk perception). Increasing the full price of one good should decrease participation and induce a change in other goods’ participation through changes in the relative prices. Assume that market prices and information have the same e¤ect on the full price (e.g. a “bad” information about cannabis increases its full price). Then, knowing the cross and direct price e¤ects, we can show that information e¤ect through full price is often counterbalanced by variations of instantaneous preferences. Using additional assumptions about the e¤ect of information providers on the full prices of alcohol and cannabis, it is then worth wondering wether our information dummies are correlated with participation solely through their e¤ect on full prices. Teenagers’ preferences are quite unstable, because adolescence is a period of role transition from childhood to adulthood 27 . Therefore, one may suppose that the more an information provider a¤ects participation through changes of full prices, the more its e¤ect will last as it means that perception of the true health risks have been modi…ed. By contrast, the e¤ect of an information on instantaneous preferences shall vanish quickly. One can also argue that it is important to keep youths’ preferences “under pressure” as they are more likely to be in‡uenced by peers during periods of role transition. But from a …nancial point of view, such a strategy is more expensive than a “once-for-all” one. In the next subsection, I attempt to estimate indirectly the signs of the price e¤ects. I use these results to assess the e¢ciency of public information providers on the one hand, and private ones on the other hand. 6.2 The e¤ect of full prices In the absence of cross-sectional prices, I estimate for each class (by using probability weights) a duration model for the age of initiation into cannabis (table 4, annex B). It is quite clear that such a model performs po orly on our data, as we face sample selection problems 28 . I use the time series of year relative price indices of alcohol and tobacco to infer the sign of the correlation between prices 2 7 Phenomenological consumer researchs show that compulsive consumption acts are intensi…ed during periods of role transition (see for an e xample Hirschman, 1992). 2 8 As noticed previously, we do not observe teenagers on the whole period where they are at risk for initiating consumption. 17 Alc. Bev. 19 97 19 94 19 91 19 88 19 85 19 82 19 79 19 76 Tobacco 19 73 Relative price index 19 70 1,6 1,4 1,2 1 0,8 0,6 0,4 0,2 0 Year Figure 2: Price index of alcoholic beverages and tobacco de‡ated by the consumer price index (source: INSEE) and the age of initiation (cf. graphic 2). I also control for generation e¤ects, puberty and gender. The price e¤ects are strongly positive for the …rst type : age of initiation increases with prices. Hence, the cross-price e¤ect of alcohol on cannabis participation is negative for class 12 9 . As the e¤ect of income on participation is null, this implies that heavy drinking and cannabis smoking are hicksian complements. Cross-price e¤ects are negative but somewhat unsigni…cant for types 2 and 3. Goods are likely to be hicksian substitutes for the latter, but complement for the former. Table 5 in annex C show the signs of the marshallian direct and cross-price e¤ects obtained from our estimates. I use it to predict the e¤ect of full prices on cannabis and alcohol participation, although the sign of some price e¤ects is not well determined (as emphasized by the question marks in the tables). 6.3 School and the medias Suppose that the medias and school increase the full prices of both alcohol and cannabis. It is easily seen that the observed and predicted signs of the cross-price e¤ects of alcohol price on cannabis participation are opposite for 2 9 There is consumption when the ratio of the relative marginal utilities of cannabis and heavy drinking is higher than the ratio of relative full prices. If zero consumption has no speci…c de terminants, this condition is tantamount to x¤ (¼A ; ¼C ; X C (t)) > 0 where x¤ () is the latent marshallian demand function (i.e. the solution of the …rst-order optimisation condition in the absence of Kuhn and Tucker’s multiplicators). 18 the …rst group (Tables 6 and 7). This means that media information about alcohol a¤ects the instantaneous preferences of these teenagers. However, school information could also decrease the full price of alcohol and increases cannabis price. Using arguments developped in section 2, we can eventually state that either school information about alcohol is not credible or it impacts both youths’ preferences and (anticipation of) full prices. In either case, it may be partially ine¢cient. Nevertheless, the cumulate e¤ect of school information about alcohol and cannabis is negative on both alcohol and cannabis participations. Hence, school informations about drugs and alcohol shall not be delivered separately, even if evidence are mixed about their e¤ect on full prices and, as a consequence, perceptions of the true health risks. We can achieve the same conclusion for the medias. The second group is more responsive to information. School information incites globally these teenagers to substitute alcohol and cannabis in favour of this latter. Moreover, it is not signi…cantly correlated with heavy drinking. If we interpret our results strictly, we should conclude that this substitution e¤ect is not a price e¤ect and consequently, that for the second type, school information is totally ine¢cient. However, if we are less bothered about the signi…cativity of our results (and ignoring the question marks in the tables), we see that school information may increase the full prices of both goods. The total e¤ect of school information about drugs and alcohol is positive. Hence, school information may have a preventative and lasting e¤ect (through changes of risks perceptions), if it concerns only cannabis. This result contradicts our …nding for the …rst group. The medias necessarily a¤ect preferences for cannabis. They have an overall (perhaps not durable) negative impact on heavy drinking and cannabis use. Compared to the second group, information has less e¤ect on the behaviours of the youths from the third group. It turns out that school information could change the participation probability through full prices if it lowered them (cf. tables 10 and 11 ). I think that it is unlikely to be case, which means that this information provider modi…es especially the preferences. It has however a preventative e¤ect, like the medias, which also induces variations of preferences. 6.4 Friends and the family Information from friends should decrease the full prices. For the …rst group, its impact on cannabis participation is slim, probably because youths from this group have little accointances with drug users. It has also no e¤ect on youths from the third class. For these two groups, straight comparisons between price and information e¤ects show that information from friends alters mainly the preferences. This is not true for the teenagers of the second group. Peer information increases their odds for both heavy drinking and cannabis. This e¤ect is compatible with a decrease of full prices, although friends may also in‡uence preferences. Such …ndings are not surprising, as there are more users in the second class and as the individuals from a same class are likely to match in the 19 same peer groups. What we observe could just be the correlated or context e¤ects described by Manski (1995). For the …rst group, family information is not correlated with consumption, even though this kind of youths has as many discussions within family as other types do. Perhaps information from the family is not credible. But, we shall interpret this result carefully, as there are few drug users in the …rst class. For the second group, there is no doubt that family information has a counterproductive e¤ect (table 9). As emphasized in section 2.2, just arguing that cannabis is a “bad”, may result in a lost of credibility. However, using table 8, we see that our results are not compatible with any kind of price e¤ect. A more traditional interpretation is that the teenagers are often reluctant to do what their parents expect them to do. This “psychological” will to break taboos could push them to act in contrast with parental opinions and desires, by changing their preferences. I have investigated the relationship between class belonging and qualitative variables capturing family dysfunctions. It is not surprising that the youths from the second and the third groups are more likely to have relational problems with their parents (little interest of the father as felt by the youth, family life that looks rather stressing or unpleasant). However, family information has little e¤ect on the behaviours of the third group. 7 Concluding comments Using cross-section data about the health and lifestyle of French teenagers, I investigated the correlations between information and cannabis consumption. I proposed a latent class probit model that accounts for the heterogeneity in the coe¢cients of interest. I assumed that this heterogeneity arises because the true model is a mixture of di¤erent probit models. Results show that there were in 1993 three latent classes, which represented respectively 58%, 23% and 19% of the population. The …rst class gathered teenagers that were less prone to smoke tobacoo, cannabis or drunkenness. They were less risk adverse, because less involved in risky behaviours. Both other classes contained more consumers (about 30% each). But the third class was more alcohol-oriented, in the sense that the propension to heavy drinking is much higher. Moreover, they drunk during social events (with friends or within family), whereas the youths who belonged to the second class were more likely to drink alone and when they feel depressed. Two general conclusions can be drawn from this study. First, the e¤ect of public policies is heterogeneous which impede the design of e¢cient general public policy. By instance, recurrent campaigns at school against drugs and alcohol would have a preventative e¤ect for the …rst and the third groups (the participation probability will fall respectively from -0.3% and -52%), but an incitative one on the second group(+23.5%)3 0 . The “real” e¤ect would be a 3 0 For each group, we can simulate the e¤ect of …nite changes in school informations about drugs and alcohol, by computing the di¤erences in probability as the value of the two variables 20 decrease of 4.8% in prevalence with unexpected consequences for the youths who are more likely to belong to the second group. Second, information does not a¤ect only the full prices of alcohol and drugs (i.e. perceptions of future health risks) but also the instantaneous preferences of users. Thus, information at school must be provided every year which may reveal costly. 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(1993), “A Simple Estimator for Simultaneous Models with Censored Endogenous Regressors”, International Economic Review, 34 (2), 441-457. 24 A Descriptive statitistics 0,18 0,16 0,14 0,12 0,1 0,08 0,06 0,04 0,02 0 9 10 11 12 13 14 15 16 17 18 19 20 21 Empirical hazard of initiation into cannabis or drunkeness Tables A2: % of good prediction from the bivariate probits for instrumentation Information variable % Family / drugs School /drugs Friends / drugs. Medias / drugs Family / alcohol School / alcohol Friends / alcohol Medias / alcohol 58.4% 70.3% 61.6% 66.8% 58.6% 76.3% 75.9% 72.4% 25 Table A1: description of the variables Variable name Variable label CANAN ALCAN Sex Pub. Age Inc1000 =1 if initiated into cannabis =1 if initiated into drunkenness (heavy drinking) =1 if male =1 if pubescent Age Monthly pocket money (in 1993 FF)/1000 Rate of initiation into cannabis in the same geographical cell (educationnal area * town/country) Rate of drunkennesses in the same geographical cell =0 if not initiated into cannabis else = (age at time of the survey- min(age of initiation+1;age at time of the survey) =0 if not initiated into heavy drinking else = (age at time of the survey- min(age of initiation+1;age at time of the survey) Has had or followed a discussion about drugs within the family Has had or followed a discussion about drugs at school Has had or followed a discussion about drugs with friends Has had or followed a discussion about drugs in the medias Has had or followed a discussion about alcohol within the family Has had or followed a discussion about alcohol at school Has had or followed a discussion about alcohol with friends Has had or followed a discussion about alcohol in the medias RateCan RateDrunk DURCAN DURDRUNK INFCANfa INFCANsc INFCANpe INFCANmed INFALCfa INFALCsc INFALCpe INFALCmed Mean (N=6534) 12.8% 27.9% 47.6% 90.2% 16.17 (se: 1.96) 0.17 (se: 0.46) 0.12 (se: 0.08) 0.23 (se: 0.06) 0.20 (se: 0.72) 0.56 (se: 1.16) 46.8% 29.9% 52.6% 34.4% 49.2% 23.7% 54.9%% 27.6% In the cell (row=X, column=Y), one reads Pr(XjY). Sociodemographic caracteristics Total sample (N=6534) Type 1 Type 2 Typ e 3 Fath. farmer Fath. Fath. crafts./ret.worker Moth. farmer Moth. up. occ. Moth. worker Moth. at home Inc. 0 Inc. 0100 Inc. 100500 Inc. 500 + Type 1 Type 2 Type 3 Male Age Father farmer Fath. craftsman or retailer Fath. upper occupations Fath. int. occ. Fath. clerks Fath. worker Fath. retired Fath. other occ. Mother farmer Moth. craft./ret. Moth. upper occ. Moth. int. occ. Moth. clerks Moth. worker Moth. at home Moth. other occ. Monthly income (1993 french francs) 58,2% 22,7% 19,1% 47,6% 16,178 1,9% 9,8% 1 0 0 45.6% 16.02 1.7% 9.2% 0 1 0 51.5% 16.26 2.0% 10.0% 0 0 1 49.3% 16.56 2.4% 11.4% 52,3% 24,1% 23,7% 54,4% 23,3% 22,3% 63,1% 22,2% 14,7% 53,3% 25,2% 21,4% 52% 23,8% 24,2% 62,2% 20,9% 16,9% 63,7% 20,6% 15,8% 63,6% 21,0% 15,4% 50,0% 24,8% 25,1% 42,2% 33,2% 24,5% 14,5% 13.9% 15.5% 15.3% 17,0% 13,5% 26,7% 3,2% 14,6% 1,2% 3,7% 6,1% 14,5% 29,8% 4,4% 29,0% 11,8% 170 16.6% 13.4% 28.0% 3.3% 15.0% 1.3% 3.4% 5.6% 14.0% 29.2% 3.9% 31.0% 12.0% 144 17.8% 13.2% 25.5% 3.0% 14.2% 1.2% 4.0% 6.7% 16.2% 30.2% 4.6% 26.6% 11.0% 209 17.4% 13.9% 24.0% 2.9% 13.8% 0.9% 4.4% 6.8% 14.1% 31.1% 5.6% 25.6% 12.1% 202 61,0% 21,7% 17,2% Family structure Total sample (N=6534) Type 1 Type 2 Typ e 3 Par. mar. Par. déc. Par. sep. Monop. fam. Recomp. Not family living with parents Type 1 Type 2 Type 3 Parents are married One of both natural parents deceased Parents are separated 58,2% 22,7% 19,1% 79,4% 4,0% 1 0 0 81.5% 3.7% 0 1 0 79.0% 3.8% 0 0 1 75.9% 4.4% 59,4% 22,5% 18,2% 55,8% 22,3% 21,9% 52,8% 24,1% 23,2% 54,8% 23,5% 21,7% 51,7% 23,6% 24,7% 16,6% 14.8% 17.2% 19.7% Single-parent family 13,4% 12.3% 13.5% 14.8% Family has been recomposed Vit hors-foyer 5,8% 5.1% 6.0% 7.4% 2,6% 2.1% 2.6% 2.7% Type 1 Type 2 Type 3 Is patient Ends what she has begun to do (time consistency) Has often a positive state of mind Has rarely had thoughts of suicide Is rarely desesperate when thinking about the future Has sexual intercourses without sheath and changes of partner are frequent Number of road accidents Nb. of sport accidents Family life is unpleasant 52,1% 25,2% 22,7% Total sample (N=6534) Type 1 Type 2 Type 3 Patient Consistent State of mind DesesperateRisky for the sexual fut. intercourses Has had a road acc. Has had a sport acc. 58,2% 22,7% 19,1% 60,9% 68,1% 1 0 0 64.1% 69.6% 0 1 0 58.4% 65.3% 0 0 1 54.3% 66.9% 61,1% 21,8% 17,1% 59,4% 21,8% 18,8% 59,9% 22,4% 17,7% 49,5% 26,0% 24,6% 54,0% 24,1% 21,9% 86,5% 87.2% 86.5% 84.4% 89,9% 91.8% 88.4% 86.1% 75,4% 77.7% 74.4% 69.7% 2,1% 1.2% 3.7% 2.9% 17,0% 0.11 0.22 0.27 57,2% 14,3% 0.51 11.7% 0.61 16.2% 0.72 19.8% 58,6% 22,8% 18,7% 33,1% 40,6% 23,3% Informations Family / drugs School /drugs Friends / drugs Medias / drugs Family / alcohol School / alcohol Friends / alcohol Medias / alcohol Type 1 46.1% 30.0% 46.8% 33.9% 47.8% 22.7% 48.1% 26.9% Type 2 47.3% 29.2% 57.9% 34.7% 50.7% 25.1% 59.9% 28.6% Type 3 48.3% 30.4% 63.7% 35.6% 51.4% 25.3% 69.4% 28.7% Drinking & Smoking Behaviours Total sample (N=6534) Type 1 Type 2 Typ e 3 ALCAN Type 1 Type 2 Type 3 Smoking initiation Regular smoker Has still smoked cannabis CANAN CANAN ¸ 10 Drinking initiation 58,1% 22.7% 19,2% 54,0% 19,7% 15,0% 1 0 0 41.3% 9.9% 3.5% 0 1 0 64.0% 29.2% 30.5% 0 0 1 80.8% 38.5% 31.4% 9.5% 33.1% 57.3% 12,8% 4,2% 77,8% 36,2% 2.3% 1.4% 68.9% 10.3% 27.0% 9.6% 83.0% 53.4% 27.6% 6.5% 98.9% 94.8% 27,9% 3,7% 4.6% 1.1% 40.7% 8.4% 83.8% 6.1% Has still drunk ALCAN ALCAN ¸ 10 been ALCAN ¸ 10 17.8% 51.1% 31.1% CANAN 10.6% 48.1% 41.3% CANAN ¸10 Heavy drinking / peers Heavy drinking / alone 18.9% 51.6% 29.5% 12.8% 38.8% 48.4% 23.7% 43.8% 32.5% Heavy drinking / bad state of mind 22.4% 45.9% 31.7% Heavy drinking / family HEavy drinking / annoyed 27.8% 31.8% 40.4% 24.0% 39.7% 36.3% B Estimates Table 1: Semiparametric mo del for cannabis use in the past year Variables Probit / CANAN – type 1 PROBIT / CANAN – type 2 PROBIT / CANAN – type 3 Sex 0,385* (0,233) 0,710*** (0,096) 0,407*** (0,096) Pub. -0,360 (0,244) 0,139 (0,153) -0,020 (0,174) Age 3,511*** (0,785) 4,707*** (0,476) 0,249 (0,418) 2 Age -0,112*** (0,023) -0,129*** (0,014) -0,013 (0,012) Inc/1000 -0,074 (0,122) -0,275*** (0,093) 0,190** (0,096) RateCan -3,312* (1,413) 1,622*** (0,547) 2,374*** (0,551) DURCAN 1,714*** (0,127) 1,288*** (0,093) 2,463*** (0,186) DURCAN2 -0,154*** (0,019) -0,220*** (0,025) -0,707*** (0,070) DURDRUNK 0,895*** (0,096) 0,017 (0,063) 0,214** (0,091) DURDRUNK 2 -0,072*** (0,016) -0,012 (0,014) -0,136*** (0,031) INFCANfa -0,306 (1,909) 3,462*** (0,854) 0,672 (0,812) INFCANsc -8,637*** (1,966) -2,809*** (0,858) 0,081 (0,843) INFCANpe 2,649 (1,931) 4,929*** (1,001) 1,655* (0,944) INFCANmed -2,728 (2,477) -4,254*** (1,076) 1,924* (1,023) INFALCfa -0,357 (1,517) -1,903** (0,814) -1,020 (0,801) INFALCsc 6,119*** (1,986) 3,551*** (0,899) -2,311** (0,961) INFALCpe -2,126 (1,600) -2,162*** (0,813) 1,020 (0,776) INFALCmed 4,757** (2,189) 1,759* (1,004) -2,028** (1,009) Constant -29,762*** (6,564) -45,104*** (4,068) -2,700 (3,520) Probability weights 58,14% 22,74% 19,12% Number of observations 6534 6534 6534 Wald Chi-2 643.77 969.25 349.09 Standard errrors in parentheses: *=signi…cant at the 10% level; **=signi…cant at the 5% level; ***=signi…cant at the 1% level Table 2: Semiparametric model for heavy drinking in the past year Variables PROBIT / ALCAN – type 1 PROBIT / ALCAN – type 2 PROBIT / ALCAN – type3 Sex 0,326** (0,138) 0,327*** (0,086) 0,567*** (0,083) Pub. -0,073 (0,224) -0,141 (0,139) 0,018 (0,121) Age 0,795* (0,449) 6,038*** (0,345) 1,291*** (0,301) Age2 -0,030** (0,013) -0,166*** (0,010) -0,037*** (0,009) Inc1000 -0,189* (0,102) -0,056 (0,077) -0,205** (0,102) RateDrunk -0,467 (1,356) 3,810*** (0,809) 1,187 (0,832) DURCAN 0,669*** (0,116) -0,116 (0,090) -0,052 (0,101) DURCAN2 -0,059*** (0,022) 0,057** (0,025) -0,052* (0,029) DURDRUNK 1,505*** (0,066) 0,868*** (0,054) -0,026 (0,067) DURDRUNK 2 -0,121*** (0,010) -0,145*** (0,013) -0,105*** (0,020) INFCANfa 0,930 (1,221) -2,263*** (0,718) 0,096 (0,692) INFCANsc -3,525** (1,580) -0,469 (0,902) -2,471*** (0,904) INFCANpe 2,459* (1,283) 1,698** (0,808) 1,417* (0,814) INFCANmed -5,009*** (1,476) 0,825 (0,911) -0,245 (0,879) INFALCfa -1,184 (1,132) 2,106*** (0,711) 1,866*** (0,687) INFALCsc 2,893* (1,645) -1,079 (0,995) 2,916*** (0,971) INFALCpe 2,596** (1,071) 1,254* (0,644) -0,769 (0,660) INFALCmed 1,058 (1,397) -2,828*** (0,848) -0,788 (0,831) Constant -9,002** (3,679) -56,313*** (2,918) -11,379*** (2,470) Number of observations 6534 6534 6534 Wald Chi-2 1170.47 1748.92 461.65 Standard errrors in parentheses: *=signi…cant at the 10% level; **=signi…cant at the 5% level; ***=signi…cant at the 1% level Table 3: Age of iniation into cannabis or drunkenness: semiparametric duration model Variables Duration - typ e 1 Sex -0,406*** (0,047) Parents not separated 0,169*** (0,055) Generation 80-81 -0,221* (0,119) Generation 79-80 0,059 (0,092) Generation 77-78 0,176** (0,079) Generation 76-77 0,281*** (0,083) Generation 75-76 -0,001 (0,079) Generation 74-75 -0,073 (0,084) Generation 73-74 -0,327*** (0,097) Generation 72-73 -0,059 (0,132) Constant 3,183*** (0,082) Ancillary parameter - loglogistic law 0,521*** (0,017) Number of observations 6534 Wald Chi-2 120.14 Standard errrors in parentheses: **=signi…cant at the 5% Duration - type 2 Duration - type 3 -0,077*** (0,010) 0,001 (0,006) 0,026** (0,012) 0,013* (0,007) -0,142*** (0,035) -0,294*** (0,026) -0,007 (0,026) -0,156*** (0,014) -0,336*** (0,019) 0,148*** (0,009) -0,246*** (0,019) 0,276*** (0,009) -0,152*** (0,018) 0,375*** (0,009) -0,119*** (0,020) 0,446*** (0,011) -0,062*** (0,021) 0,522*** (0,014) 0,052** (0,025) 0,545*** (0,025) 2,110*** (0,018) 1,693*** (0,009) 0,137*** (0,003) 0,077*** (0,002) 6534 6534 621.73 4707.91 level; ***=signi…cant at the 1% level Table 4: Age of initiation into cannabis - weighted duration analysis Variables Type 1 Sex -0,695*** (0,125) Pub. -0,469*** (0,137) Parents not separated 0,266*** (0,087) Generation 80-81 0,355 (0,365) Generation 79-80 0,397 (0,247) Generation 77-78 0,225 (0,140) Generation 76-77 0,468*** (0,144) Generation 75-76 0,082 (0,124) Generation 74-75 -0,015 (0,141) Generation 73-74 -0,285* (0,156) Generation 72-73 0,044 (0,205) Relative price index of alcohol 11,212*** (1,835) Relative price index of tobacco 1,835** (0,778) Constant -9,266*** (1,944) Ancillary parameter - loglogistic law 0,461*** (0,061) Standard errrors in parentheses: **=signi…cant at the 5% Type 2 Type 3 -0,126*** (0,022) -0,017 (0,018) -0,044 (0,028) -0,075** (0,029) 0,076*** (0,021) 0,072*** (0,021) 0,194 (0,191) -0,240*** (0,076) 0,374*** (0,111) -0,100** (0,039) -0,365*** (0,059) 0,072** (0,032) -0,337*** (0,065) 0,215*** (0,033) -0,276*** (0,071) 0,293*** (0,037) -0,248*** (0,083) 0,393*** (0,046) -0,195** (0,090) 0,513*** (0,051) -0,072 (0,104) 0,461*** (0,091) -1,488 (1,117) -2,467* (1,318) -0,877 (0,651) -0,669 (0,540) 5,005*** (1,830) 5,313*** (1,872) 0,183*** (0,013) 0,162*** (0,016) level; ***=signi…cant at the 1% level C Price and information e¤ects @xC @pA ² is the derivative of the marshallian cannabis demand with respect to the price of alcohol (obtained from table 4). ² @xC @y is the income e¤ect for cannabis participation (obtained from table @h C @pA is the derivative of the hicksian cannabis demand with respect to the ² 1). price of alcohol. By Slutski equation: @hC @p A = @xC @p A C + x A @x @y . ² As the matrix of hicksian price e¤ects is symmetric: ² ² @xA @y @hC @ pA = @hA @ pC . is the income e¤ect for drunkenness participation (obtained from table 2). @xC @pA is the derivative of the marshallian alcohol demand with respect to A A A price of cannabis: @x = @h ¡ x C @x . @p C @ pC @y Table 5: Signs of direct and cross price e¤ects @xC @xC @hC @h A @xA @xA @p A @y @ pA = @ pC @y @ pC Type 1 -*** 0 -* ? Type 2 0 (+?) -*** -? 0 -? Type 3 +* +** + -** + Let ¼ A and ¼ C be respectively the full prices of alcohol and cannabis: i sign( @@¼xji ) = sign( @x ); i; j = A; C. The following tables show the predicted @p j signs of correlations between information and consumption if informations a¤ect consumptions only through changes of full prices. Table 6: Predicted signs of the direct and cross information e¤ects: type 1 Participation decision Information about... ¼ A %; ¼ C % ¼ A &; ¼ C % ¼ A %; ¼ C & ¼ A &; ¼ C & ALCAN Alcohol Cannabis ? + ? ? + ? CANAN Alcohol Cannabis + + + + Table 7: Observed signs of the direct and cross information e¤ects: type 1 33 Participation decision Information about... from school from friends from the family from the medias ALCAN Alcohol Cannabis +* -** +** +* + + -*** CANAN Alcohol Cannabis +*** -*** + +** - Table 8: Predicted signs of the direct and cross information e¤ects: type 2 Participation decision ALCAN CANAN Information about... Alcohol Cannabis Alcohol Cannabis ¼ A %; ¼ C % -? +?. ¼ A &; ¼ C % + -? -? ¼ A %; ¼ C & +? +? + ¼ A &; ¼ C & + +? -? + Table 9: Observed signs of the direct and cross information e¤ects: type 2 Participation decision ALCAN CANAN Information about... Alcohol Cannabis Alcohol Cannabis from school +*** -*** from friends +* +** -*** +*** from the family +*** -*** -** +*** from the medias -*** + +* -*** Table 10: Predicted signs of the direct and cross information effects: type 3 Participation decision Information about... ¼ A %; ¼ C % ¼ A &; ¼ C % ¼ A %; ¼ C & ¼ A &; ¼ C & ALCAN Alcohol Cannabis + + + + - CANAN Alcohol Cannabis + + + + Table 11: Observed signs of the direct and cross information effects: type 3 Participation decision ALCAN CANAN Information about... Alcohol Cannabis Alcohol Cannabis from school +*** -*** -** + from friends +* + +* from the family +*** + + from the medias -** +* 34