Underage faculty college students who receive and use false identification (fake ID) are at risk for adverse outcomes. Nevertheless, it is at present unclear how uniquely the fake ID itself serves as a vehicle to subsequent hurt (i.e., the “fake ID impact”) over and above common and trait-related risk elements (e.g., deviant friends, low self-management).


With a purpose to examine whether or not the “fake ID impact” would hold after accounting for phenotypic risk, we utilized propensity rating matching (PSM) in a cross-sectional pattern of n=1,454 college students, and a longitudinal replication pattern of n=three,720 undergraduates. Individuals with a fake ID have been matched with people with out a fake ID, by way of numerous trait-based and social risk factors. These matched teams have been then in contrast on 5 problematic outcomes (i.e., frequent binge ingesting, alcohol-related problems, arrests, marijuana use, and hard drug use).



Findings confirmed that “fake ID effects” have been considerably—though not totally—diminished following PSM. The “fake ID impact” remained strongest for alcohol-related arrests. This may increasingly relate to issues of enforcement and college students’ willingness to engage in deviant behavior with a fake ID, or it could be a perform of combined processes.


General, the findings suggest that interventions should not solely be aimed at decreasing fake ID-related alcohol entry specifically, but must also be aimed more usually in direction of at-risk youths’ entry to alcohol. Future analysis might examine whether or not fake IDs have their strongest efficiency as moderators of the consequences of dangerous traits—such as impulsiveness—on ingesting outcomes.

Keywords: False identification, Fake IDs, underage alcohol use, heavy episodic ingesting, binge ingesting


Fake IDs, a singular mode of alcohol entry, are more and more sought after as people close to the minimum authorized ingesting age (Martinez et al., 2007; Wagenaar et al., 1996). These types of false identification may be borrowed (or duplicated) from an older peer or sibling (Myers et al., 2001), or they could be a specially crafted document obtained regionally or from a web based vendor (Murray, 2005). No matter their source, there seems to be a bidirectional relation between heavy ingesting and fake IDs, such that (1) heavy ingesting predicts subsequent obtainment of a fake ID, and (2) “ownership” (i.e., possession) of a fake ID predicts subsequent frequency of heavy ingesting (outlined as 5+ drinks per occasion; Martinez, et al., 2007).

This bidirectional relation not solely illustrates the general public health risks of this mode of alcohol entry, but begs the question of whether or not it is more the case that a fake ID itself serves as a vehicle to subsequent hurt (i.e., the “fake ID impact”) or whether or not such harms and outcomes are predominantly pushed by a common stage of phenotypic risk on the part of the fake ID “proprietor” (e.g., deviant peer associations, low self-management). Although common alcohol entry theories might support the former hypothesis virtually fully (specifically, fake ID possession will increase alcohol entry and subsequent hurt; see Gruenewald, 2011), common criminological theories of phenotypic risk support the latter (specifically, that broad categories of risk—or propensities to engage in dangerous behavior—are the true reason for hurt; see Pratt & Cullen, 2000). Certainly, such propensities is perhaps what predicts fake ID obtainment in the first place, and though the energy of the fake ID impact seems to extend over time, it is tremendously diminished after controlling for sex, Greek status, and pre-faculty charges of ingesting (Martinez et al., 2007). In sum, it is unclear how sturdy the fake ID impact is perhaps after accounting for individuals’ ranges of phenotypic or propensity risk—though this question has bearing on prevention and coverage initiatives, which can deal with both strengthening enforcement of fake ID legal guidelines themselves, increasing sources for trait-based at-risk youth programs, or a group-pushed combination of both (see Fell, Thomas, Scherer, Fisher & Romano, 2015; Fell, Scherer, Thomas & Voas, 2016; Fell, Scherer & Voas, 2015; Grube, 1997) .

Thus, to be able to examine the energy of the fake ID impact, we matched college students with and with out fake IDs on numerous risk-based covariates using propensity rating matching (PSM) techniques. We first in contrast matched teams’ ingesting- and drug-use-related outcomes in a cross-sectional pattern of n=1,454 faculty college students at a big Southeastern university. We also in contrast matched teams in an additional longitudinal replication pattern of n=three,720 undergraduates at a big Midwestern university. We hypothesized that the consequences of fake ID ownership on outcomes can be tremendously diminished by—and due to this fact largely attributable to—the pre-present trait-based elements on which fake ID house owners and non-house owners might be matched. These comparisons can inform the extent to which the connection between adverse outcomes and false identification ownership are attributed to choice elements, which once more, might have sensible software for intervention and policy.

Process and Members

Two samples have been separately investigated following Institutional Overview Board (IRB) approval: (1) A cross-sectional pattern of n=1,454 underage faculty college students from a big Southeastern University (IRB Protocol H12032) and (2) a potential replication pattern of n=three,720 undergraduates below the minimum authorized ingesting age from a big Midwestern university (IRB Protocol 01-01-001). Of observe, both samples provide distinctive insights into the connection between false identification use and adverse outcomes. Extra specifically, the cross-sectional examine includes items that distinguish between the use of fake IDs in different conditions (at bars, at grocery shops, etc.) and the longitudinal examine gives perception into the potential effects of fake ID ownership over time and establishes temporal order.

With regard to the cross-sectional pattern, in the course of the tutorial year 2011–2012, members have been recruited from forty randomly chosen massive (>99 college students) and moderate enrollment (30–99 college students) classes. Members completed a one-web page informed consent document in the chosen classes before being given a six-web page paper survey about faculty life and behaviors to complete with pencil or pen. Members weren’t compensated. All enrolled college students have been invited to take part and the response price was high at 80.four% (Stogner & Miller, 2013; 2014; Hart et al., 2014). After these above the authorized ingesting threshold have been removed, the analytic pattern was n=1,454 underage individuals. The pattern was largely representative of the university with regard to demographics and was specifically 51.6% feminine, 68.9% White/non-Hispanic, with a median age of 18.ninety five (SD=.795). Although this pattern is cross-sectional, establishing temporal ordering of the covariates and fake ID ownership is basically inconsequential for the majority of covariates as many are immutable (age, race, gender) or outdoors of the person’s management (home location, parental earnings, sexual orientation, etc.).

The longitudinal pattern also utilized a self-report survey methodology. All incoming college students in 2002 have been recruited to complete an instrument in the course of the summer time prior to university entrance using paper and pencil and then have been requested to complete on-line surveys every semester for the next four years (a total of eight semesters). Students offered informed consent and have been compensated $25 in every wave. After excluding the n=35 who have been of age, 88% of the eligible coming into class completed the survey (n=three,720). The pattern was 53.7% feminine, 90.three% White/non-Hispanic, and averaged 17.9 (SD=.36) years of age (reflecting demographics that are representative of the university as a whole [University Registrar, 2013]). Students have been historically aged; by the beginning of their junior year, just one-third of the pattern had reached the minimum authorized ingesting age, climbing expectedly to 99.7% by the final semester of school, Pattern retention was good, starting from sixty nine% to 87% of baseline respondents taking part at every subsequent wave. Retention biases have been low, though people have been more more likely to remain in the pattern in the event that they have been females (OR=2.33) and have been less more likely to remain in the pattern in the event that they have been frequent binge drinkers (OR=.88; Sher & Rutledge, 2007). By the final time-point, the pattern dimension was n=2,250, though 90% of students participated in two or more evaluation waves and 82% participated in three or more waves. The longitudinal PSM presented throughout the textual content utilized the primary two years of school solely (i.e., the primary four semesters, when the overwhelming majority of members have been underage) and, consistent with most PSM analysis, solely created matches between people in a fashion which is straight corresponding to the evaluation carried out with the cross-sectional sample.1


For the purposes of replication, it was necessary that the measures used in both the cross-sectional and longitudinal research stayed as similar as possible. For ease of presentation, measures are organized by way of their conceptual importance to the overall examine with cross-sectional and longitudinal measures defined collectively in every section. Timing of the longitudinal measures was thought of necessary and is described as is appropriate. Specifically, though the eight-wave longitudinal pattern included a number of measurements of many covariates throughout time, the first longitudinal PSM solely utilized measurements as they might be expected to occur if observing a “fake ID impact” over a logical development of time (i.e., Trait/propensity measures have been measured at Wave 1 and used to predict fake ID ownership at Wave 2 which in turn assessed as a predictor for final result measures at both Waves three and Wave four). The second semester of school (Wave 2) was chosen as the singular goal time-point at which fake ID ownership (or the “fake ID impact”) was measured, as a result of it is considered a peak time of risk for adverse ingesting-related outcomes and false ID ownership (see Martinez et al., 2008).

Essential Outcomes 5 outcomes related to substance use have been explored. First, a measure of frequent binge ingesting was created in both samples. A six-choice ordinal item requested respondents how many days in the final month did they eat 5 or more alcoholic drinks. A sex-specific binge ingesting measure was not available. These choosing both of the 2 highest frequency options (10–19 days and 20+ days) have been classified as frequent binge drinkers whereas all others have been not. This dichotomous item represents binge ingesting greater than ten days in the final month. Second, we utilized an instrument created by Maney, Higham-Gardill, and Mahoney (2002) to signify alcohol-related problems in the cross-sectional sample. This ten-item scale assesses the degree to which the person feels that alcohol use has created relationship, family, health, behavioral, and professional/faculty problems in the final year and shows sufficient reliability (α=.822). Within the longitudinal pattern, this scale was approximated from ten items taken from the Younger Adult Alcohol Issues Screening Test (YAAPST; Hurlbut & Sher, 1992) with sufficient reliability (α=.848 in second-year fall and α=.846 in second-year spring). A dichotomous alcohol-related arrest/citation measure was created inside both samples using items that requested respondents if they had ever been arrested or cited for driving below the affect, underage ingesting, public dysfunction (because of alcohol), being drunk in public, or an open container violation in the final year. The final two outcomes have been both dichotomous and measured equally in every pattern; marijuana use and hard drug use signify whether or not the respondent self-reported any use of marijuana and cocaine, heroin, and/or methamphetamine, respectively, in the final year.

False Identification Current fake ID “ownership” was assessed dichotomously in both samples (0=No, 1=Yes). The cross-sectional examine also included further items that requested respondents whether they had used the fake ID in a bar or club and whether they had used it in a retailer to purchase alcohol.

Trait and risk issue (matching) covariates Fifteen variables have been used in propensity rating matching in the cross-sectional pattern and fourteen have been used in the longitudinal sample. Variables have been chosen because of their inclusion in both datasets and former analysis suggesting that they could be related to the propensity to personal a fake ID and expertise one of the 5 outcomes. These matching variables are: (1) age, (2) age of alcohol use onset, (three) employment status, (four) publicity to substance use, (5) family earnings, (6) gender, (7) GPA, (8) Greek membership, (9) health, (10) low self-management, (11) peer substance use, (12) race, (13) rural home location (solely measured in the cross-sectional examine), (14) sexual orientation (1=LGBT), and (15) subjective distress.

Eight of the fifteen variables have been measured identically and a ninth was measured almost identically. Amongst these identically measured have been age, age of first alcohol use, employment status (0= not employed; 1=employed), gender (0=feminine; 1=male), self-reported grade point average (GPA), membership in a campus Greek organization (0=non-member; 1=member), race (0=white, 1=non-white), and sexual orientation (0=heterosexual; 1=lesbian, gay, bisexual, or different). Self-reported health was measured with an item that requested respondents to price their own health—the cross-sectional examine provided responses starting from 1 (poor) to four (excellent) whereas the longitudinal examine options ranged from 1 (poor) to five (excellent).

The cross sectional examine utilized four-item measures tailored from Lee, Akers, and Borg (2004) to signify publicity to substance use (α=.786) and peer substance use (α=.801). As the longitudinal knowledge didn’t include similarmeasures, every of those constructs was represented by a single item relatively than a four-item scale. The primary (publicity) was measured dichotomously whereas the second (peer substance use) was measured on a six-choice ordinal scale. Low self-management was operationalized using the 24-item Grasmick et al. (1993) scale (α=.889) in the cross-sectional examine and the NEO 5 Factor Stock conscientiousness scale (reverse-coded) in the longitudinal pattern (α=.844; Costa & McCrae, 1992). Subjective misery was measured using Cohen and Williamson’s (1988) ten-item perceived pupil stress scale (α=.814) in the cross-sectional examine and the World Severity Index from the Brief Symptom Stock-18 in the longitudinal pattern (Derogatis, 2000). Higher values on these scales signify more publicity to substance use, a larger portion of friends that use substances, lower self-management, and more subjective misery, respectively.

Both research included a single-item family socioeconomic status measure. Within the cross-sectional examine a measure of family earnings was used. Members selected between options starting from below $10,000 per year (coded 1) to over $175,000 per year (coded 9). An item assessing whether or not or not college students have been the primary of their family to attend faculty (0=No, 1=Yes) was utilized in the longitudinal study.

Rural home location was used in the cross-sectional examine, but no similar measure was accessible in the longitudinal data. This variable was necessary to include despite creating differing matching standards due to the characteristics of the examine area. The cross-sectional pattern was drawn from an space that may be very rural with the exception of one major metropolis; thus, a dichotomous item representing whether or not the scholar grew up in an urban / suburban space (coded 0) or a rural one (coded 1) was included. By comparability, this was not a particular consideration for the longitudinal pattern, which originated from a university of 35,000 that pulls college students from two massive neighboring cities and its personal moderately massive population.


First, we estimated the proportions of fake ID ownership in both the cross-sectional and longitudinal samples. In addition to possession of a fake ID, the cross-sectional pattern also documented members’ using of the fake ID in bars/clubs and stores. We estimated the bivariate associations of fake IDs with the 5 specified substance use outcomes in both samples—a rudimentary “fake ID effect.”

Next, to better determine the energy of the “fake ID impact” after accounting for trait measures, propensity rating matching (PSM) was used for both samples. PSM gives a clearer image of the connection between two variables than bivariate analyses which can yield spurious results (Guo & Fraser 2009) and has been used to evaluate points related to substance use (Miller et al., 2011). Also of observe, PSM is preferable to multivariate regression models in situations such as this where the variable of curiosity is probably not independently linked to the dependent variable, but is likely correlated with these that are and also happens more proximally. The propensity matching methods developed by Rosenbaum and Rubin (1983, 1985) can be used to create a pattern with two teams that are similar in all relevant variables aside from the “therapy” (i.e., fake ID possession). Whereas their methods do result in a reduction in dimension of analytic pattern (often leading PSM to be referred to as resampling), they are effective at creating a scenario whereby the impact of “therapy” can be estimated as the typical difference between these uncovered to the therapy and “counterfactuals,” outlined as the anticipated outcomes have been it not for publicity to the therapy (Guo & Fraser 2009). On this case, the PSM method creates analytic teams whereby variations other than false identification use are minimalized.

As recommended by Rosenbaum and Rubin (1983, 1985), we utilized logistic regression to estimate a propensity rating for every participant in every analytic sample. Fake ID possession was regressed on 15 covariates in the cross-sectional pattern (age, age of firsts alcohol use, employment status, publicity to substance use, family earnings, gender, grade point average, membership in a campus Greek organization, self-assessed health, low self-management, peer substance use, race, dimension of home group, sexual orientation, and subjective misery) and 14 similar variables (dimension of home group excluded, as defined above) in the primary longitudinal PSM evaluation (i.e. fake ID possession measured on the second semester and outcomes evaluated in the third and fourth semesters). Using these models, every participant’s propensity rating was then calculated as their conditional probability of getting a fake ID. Following an evaluation of areas of widespread support, we created comparability teams inside every pattern using a two-to-one nearest neighbor matching algorithm with a caliper calculated as .25σ of the propensity scores (see Guo & Fraser 2009). This caliper was .0725 in the cross-sectional pattern and .0426 in the longitudinal sample. This matching method led to the expected decrease in pattern dimension (n=817 and n=518, respectively) but a adequate variety of circumstances have been retained for statistical comparisons.

Rates of fake ID ownership

Rates of fake ID ownership have been fairly high, significantly in the cross-sectional sample. That is, of the 1,454 underage alcohol customers in the cross-sectional pattern, 583 or 40.1% personal or have owned a fake ID, 560 (38.5%) have used a fake ID at a bar, and 460 (27.8%) have used the ID to purchase alcohol at a store. Prevalence charges of false ID use in the Midwestern pattern modified over time. Fake ID ownership amongst college students below 21 peaked in the course of the third year of school (pre-faculty=12.5%, first-year fall=17.1%, first-year spring=21.four%, second-year fall=28.1%, second-year spring=32.2%, third-year fall=34.9%, third-year spring=39.0%, fourth-year fall=38.1%, fourth-year spring= fewer than ten college students have been below the minimum authorized ingesting age).2

The “fake ID impact” prior to matching

Desk 1 presents imply scores for 5 substance use outcomes for fake ID house owners and non-house owners in both samples (outcomes at both Wave three and four are reported for the longitudinal pattern). Average scores for every final result (frequent binge ingesting [10 or more days in the final month], self-reported alcohol related problems, alcohol-related arrests, marijuana use, and hard drug use) are presented for those who have and haven’t owned a fake ID, used a fake ID at a bar/club (cross-sectional pattern solely), and used a fake ID at a retailer (cross-sectional pattern solely). Independent samples t-tests have been performed to find out whether or not, on average, variations exist between fake ID customers and non-users. Every of the tests reached significance. No matter whether or not the focus was ownership of a fake ID or using it at a particular sort of outlet, the results have been consistent. On the bivariate stage, more people with false identification interact in frequent binge ingesting, have been arrested/cited for an alcohol violation, interact in marijuana use, and use hard drugs. Individuals with fake identification also, on average, report more alcohol-related problems. These results would indicate that fake IDs are a vehicle of risk. Nevertheless, it is potential that fake ID ownership (and related risks) are more a perform of underlying dangerous traits.

Propensity rating matching (PSM)

Due to the consistency in the findings up to now regardless of false identification measure (ownership, bar use, and/or retailer use), the additional analyses with every pattern utilizes just one false identification measure, possession of a false ID. We carried out PSM analyses in both samples, to look at whether or not people with and with out fake IDs continue to vary on these outcomes after being matched on substantively necessary traits. Desk 2 shows that people with and with out fake IDs indeed differed from each other on these trait propensity variables, suggesting that it is these variables which can ultimately be driving the fake ID effect. Desk 2 also shows that the PSM method worked nicely in both samples, constantly decreasing bias related to the statistically significant variations between these with and with out fake IDs by greater than 50% on all but one variable. Though three significant variations still remained in the cross-sectional pattern (age of alcohol use onset, Greek affiliation, and having been raised in a rural space), the magnitude of the variations in age of onset and Greek affiliation have been minor compared to pre-matching. On this, matching was equally, if no more, profitable in the longitudinal sample. It needs to be noted that matching did yield a reduction in pattern size. General, however, in both samples matching seems to have created therapy and comparability teams that are more equivalent and more applicable for comparability than the unequalled data.

The propensity scores that have been calculated for every case are graphically displayed in Determine 1. As can be seen in the determine, a area of widespread support exists, but very few with low propensity scores had a fake ID and very few with high propensity scores did not.

Evaluating fake ID house owners and non-house owners after PSM

Cross-sectional pattern After matching, false identification house owners and non-house owners have been in contrast on every of the 5 substance use related outcomes. Whereas considerably more of these with fake IDs in the cross-sectional pattern have been frequent binge drinkers prior to matching (t=9.81, df=815), the teams have been no longer considerably totally different after matching (t=1.81, df=815) and the typical therapy impact (ATE; e.g., variations in group means), as displayed in Desk three, was reduced by 59.2%. Equally, prior to matching, fake ID house owners had considerably increased scores on the alcohol related problems scale than non-house owners (t=9.eighty three, df=815), but the teams have been no longer considerably totally different after matching (t=1.31, df=815) and the ATE was reduced by 63.four%. Nevertheless, by way of alcohol-related arrests, the 2 teams have been still considerably totally different and the ATE successfully remained unchanged. As was the case for the primary two outcomes, fake ID possession was related to marijuana use prior to matching (t=9.36), but not after (t=1.fifty two; ATE reduced by 60.four%). Lastly, hard drug use was related to fake ID possession both before (t=7.26, df=815) and after matching (t=2.29, df=815), but the ATE was reduced by 38.four%.

Longitudinal pattern As was the case in the cross-sectional pattern, propensity rating matching led to a considerable decrease in the ATE for four of the 5 outcomes (Desk three, columns three–6). Nevertheless, not like the cross-sectional pattern, ATEs remained significant for alcohol related problems (t=4.00 wave three; t=4.17, wave four, df=516) and marijuana use (t=4.13, wave three; t=2.58, wave four, df=516) after propensity rating matching. The ATE also remained significant for frequent binge ingesting (t=3.26, df=516, wave three) and hard drug use (t=2.06, df=516, wave four) at one wave but not the other. Again, these effects sizes have been considerably reduced, but in the aforementioned circumstances, not eliminated. As was the case in the cross-sectional pattern, propensity rating matching had little affect on the ATE on alcohol-related arrests.three


This examine’s preliminary results are consistent with earlier analysis—a considerable variety of underage college students have fake IDs and are at increased risk for binge ingesting, alcohol-related problems, alcohol related arrests, and different substance use (see Arria et al., 2014; Martinez & Sher, 2010; Nguyen et al., 2011). But our work also confirmed that for some outcomes, it appears that evidently what initially may need seemed to be a “fake ID impact” is basically the results of elements that influenced both the acquisition of the false ID and the outcome. The numerous relationship between fake ID use and different substance use outcomes often remained after PSM, but the magnitude of those relationships have been considerably diminished, most by over 40%. Alcohol-related arrests have been an exception as the connection was unaffected by PSM (i.e., after matching, these with a fake ID have been still at equally high ranges of risk for alcohol-related arrests [DUIs, open container, etc.]). The explanation this final result is distinct from the others will not be readily clear; perhaps legislation enforcement officers usually tend to issue citations or arrests for different substance-related offenses when an individual can also be discovered with a fake ID. If so, the “impact” wouldn’t appear smaller in propensity rating models as the difference can be pushed by officers’ reactions to the fake ID relatively than people’ underlying propensity.

The pattern that emerges from Desk three seems to indicate that non-matched samples might have overestimated the impact of false identification use on adverse outcomes, but that fake ID ownership has an impact that extends beyond shared causal factors. This specific remaining “fake ID impact” might indeed support the idea that the fake ID itself serves as a sort of threshold into different types of deviant behavior, where those that are prepared to acquire fake IDs develop into more and more prepared to violate different legal guidelines (see Ruedy et al., 2013; Winograd et al., 2014). But in mild of the opposite findings, it is more doubtless that fake IDs more usually moderate the consequences of dangerous traits on behavior. For instance, fake IDs might have the best efficiency of impact through offering impulsive people with further means and opportunity for problematic behaviors that they might not otherwise have engaged in. Indeed, underlying trait risks are sometimes included into opportunity-idea-related examinations of crime (Grasmick et al., 1993; Lagrange & Silverman, 1999).

As such, these findings have sensible implications. Though elevated server training, fake ID production/supplier legal guidelines, and liability legal guidelines are an necessary means of addressing the risks of fake IDs as a form of alcohol entry (Fell, Scherer, Thomas & Voas, 2014; Yörük, 2014), faux-ID related outcomes may additionally partly be a perform of trait risks that can additionally be addressed with intervention. One option to start addressing this combination of things may be through motivational, normative suggestions-based, or abilities interventions that are specifically aimed at decreasing the chance that at-risk college students receive a fake ID (see Fromme & Orrick, 2004; Larimer & Cronce, 2007). Furthermore, a fake ID obtainment-aimed intervention might presumably be broadly included into interventions that are particularly tailor-made toward addressing both people’ dangerous traits and their resulting behaviors (see Conrod et al., 2006).

Although a great energy of this examine rests in the similar findings discovered with two distinctive faculty populations, these findings is probably not generalizable to non-faculty attending populations. Moreover, fake ID policies, enforcement, and fear of sanctions might differ considerably in different localities (Erickson, Lenk, Toomey, Nelson & Jones-Webb, 2016). For instance, some ingesting institutions may be lenient of their carding policies, deliberately accept false identification, and/or not be subject to rigorous regulatory enforcement (Murray, 2005). Also, penalties for possessing and/or using a fake ID to purchase alcohol varies considerably from state to state together with the kind of offense, quantity of superb, suspension of driver’s license, and the potential for probation or jail time. Future analysis ought to evaluate the affect of fake ID relative to differential policies and enforcement of the minimum authorized ingesting age, together with group efforts (Grube, 1997). Additional, whereas fifteen distinct traits have been included in the matching course of, there remains the likelihood that further elements not measured in our knowledge would have an effect on both the willingness to entry a fake ID and the result measures. If so, the “fake ID impact” may be even smaller than our matching models suggested.

In concluding that the “fake ID impact” is especially a perform of phenotypic risk, fake ID ownership might function an indicator of heightened risk for more extreme ingesting related problems. Although most penalties for fake ID ownership are punitive (fines, probation/jail, and/or lack of driver’s license), coverage-makers, university officials, and practitioners ought to goal fake ID house owners for intervention methods aimed at decreasing high-risk ingesting behaviors (and different problematic behaviors linked to phenotypic risk). Although elevated penalties and enforcement of the minimum authorized ingesting age has the potential to cut back fake ID ownership, we warning coverage-makers to evaluate and contemplate the adverse consequences of transferring faculty ingesting away from regulated institutions where safety and emergency providers are more readily available (see Baldwin et al., 2012; 2014). Although our findings discovered that fake ID possession (regardless of individual risk characteristics) elevated the danger for alcohol related arrests, drug use, and alcohol related problems (Midwest pattern solely), we didn’t assess victimization and different harms related to extreme alcohol consumption that would enhance in areas not subject to regulatory controls (Miller, Levy, Spicer & Taylor, 2006). Future analysis is needed to evaluate the affect that fake ID enforcement might have on problematic ingesting both in regulated and unregulated spaces.