Meta-analysis of executive functioning in ecstasy/polydrug users

Abstract

Ecstasy/3,4-methylenedioxymethamphetamine (MDMA) use is proposed to cause damage to serotonergic (5-HT) axons in humans. Therefore, users should show deficits in cognitive processes that rely on serotonin-rich, prefrontal areas of the brain. However, there is inconsistency in findings to support this hypothesis. The aim of the current study was to examine deficits in executive functioning in ecstasy users compared with controls using meta-analysis. We identified k = 39 studies, contributing 89 effect sizes, investigating executive functioning in ecstasy users and polydrug-using controls. We compared function-specific task performance in 1221 current ecstasy users and 1242 drug-using controls, from tasks tapping the executive functions – updating, switching, inhibition and access to long-term memory. The significant main effect demonstrated overall executive dysfunction in ecstasy users [standardized mean difference (SMD) = −0.18, 95% confidence interval (CI) −0.26 to −0.11, Z = 5.05, p < 0.001, I² = 82%], with a significant subgroup effect (χ² = 22.06, degrees of freedom = 3, p < 0.001, I² = 86.4%) demonstrating differential effects across executive functions. Ecstasy users showed significant performance deficits in access (SMD = −0.33, 95% CI −0.46 to −0.19, Z = 4.72, p < 0.001, I² = 74%), switching (SMD = −0.19, 95% CI −0.36 to −0.02, Z = 2.16, p < 0.05, I² = 85%) and updating (SMD = −0.26, 95% CI −0.37 to −0.15, Z = 4.49, p < 0.001, I² = 82%). No differences were observed in inhibitory control. We conclude that this is the most comprehensive analysis of executive function in ecstasy users to date and provides a behavioural correlate of potential serotonergic neurotoxicity.

Introduction

Ecstasy (3,4-methylenedioxymethamphetamine; MDMA) remains popular despite reports of potential long-term negative consequences associated with repeated use (see Parrott, 2013a , b ). Furthermore, ecstasy poses a major public health concern due to an increase in recent MDMA-related deaths (Anderson, 2014) as well as reported increases in tablet strength, with some sources suggesting tablets may contain upwards of 200 mg of MDMA (Global Drugs Survey; Winstock, 2015). Animal literature suggests that ecstasy causes damage to serotonin axons (Ricaurte et al. 1988; Molliver et al. 1990). There is also evidence of ecstasy-related alterations in mood (Curran et al. 2004) and long-term changes in neuroendocrine function (Wetherell & Montgomery, 2014). However, perhaps public health warnings are not being taken seriously due to mixed messages in the media and scientific literature about relative harms of drugs (for assessment of drug-related harms, which poorly correlate with UK drug classification, see Nutt et al. 2010).

A recent review by Murphy et al. (2009) suggests that ecstasy-related cognitive dysfunction is not consistently reported in the literature, thus monitoring of research is necessary to gain a coherent understanding of drug effects. Executive functions (EFs) have been defined as a set of general-purpose control processes, required for regulating thought and action (Miyake & Friedman, 2012). Moreover, the central executive is an integral component of working memory (Baddeley, 2000) and is required for coordinating and processing information. Some of the apparent inconsistency in the literature may be attributable to several of the classic working memory/‘executive’ tasks requiring use of multiple EFs: a problem of task impurity (Miyake & Friedman, 2012). An influential EF framework suggested that the central executive is not a unified construct; rather it is comprised of several correlated but distinctly separable functions (Miyake et al. 2000). Three discrete EFs were originally identified: mental set shifting/switching (‘switching’); information updating and monitoring (‘updating’); and inhibition of prepotent responses (‘inhibition’). A fourth component, ‘access’ to semantic memory, was later added by Fisk & Sharp (2004). These are the four classic EFs that have been assessed in the literature. However it is interesting to note that more recent developments in the unity/diversity framework (Miyake & Friedman, 2012) suggest that inhibitory control no longer exists as an EF, as it is subsumed under the concept of working memory and EF in general.

Montgomery et al. (2005a ) suggested that there may be a differential pattern of executive impairment based on previous drug use and type of function, whereby ecstasy-related deficits were apparent in updating and access, but not in switching or inhibition. These conclusions were arrived at by administering tasks that are understood to assess one function only. As such, it may be that ecstasy users are impaired on some EFs and not others, supporting the unity and diversity framework (Miyake et al. 2000; Miyake & Friedman, 2012). There are nuances in the neuroanatomy underpinning each function, which may explain why impairment is potentially function specific. For example, the dorsolateral prefrontal cortex (DLPFC) is understood to be important for memory updating (Goldman-Rakic, 1996), whereas lesion studies suggest that the left DLPFC in particular is important for letter-based word fluency (Stuss et al. 1998). Ability to switch mental set is impaired following damage to the PFC and basal ganglia (Ravizza & Ciranni, 2002), and finally response inhibition performance has long been localized to the PFC; however, of particular importance is the right inferior frontal gyrus (Chambers et al. 2009). The conclusions reached by Montgomery et al. (2005a ) and the review by Murphy et al. (2009) are that ecstasy use has a stronger detrimental effect on updating and access, and that inhibitory control and mental set switching are unaffected by use. However, there are instances of ecstasy users showing no apparent deficit in function-specific tasks that tap updating (Hanson & Luciana, 2004; Hoshi et al. 2007) and access (Gouzoulis-Mayfrank et al. 2000; Bedi & Redman, 2008) as well as instances of ecstasy-related impairments in switching (von Geusau et al. 2004; Dafters, 2006a ) and inhibition (Yip & Lee, 2005).

Several neuroimaging studies have concluded that ecstasy-related neuronal adaptations may occur neurophysiologically before they manifest functionally. Roberts & Montgomery (2015a ) suggested that ecstasy users display increased blood flow to areas of the PFC during a verbal fluency task, despite no differences in task performance. This suggests that ecstasy users work harder to achieve similar performance to controls, and that functional differences may be apparent with increased workload. Similar conclusions have been drawn from electroencephalogram studies whereby ecstasy users display evidence of recruiting additional resources in comparison with controls, whilst showing similar performance (Burgess et al. 2011; Roberts et al. 2013a , b , c ). Similarly, functional magnetic resonance imaging (fMRI) studies have shown alterations to neuronal activation consistent with ecstasy-related damage despite not showing any performance deficits (Moeller et al. 2004; Daumann et al. 2005; Jager et al. 2008; Roberts & Garavan, 2010). Such neuroimaging studies suggest that neurophysiological correlates of executive performance are present before a behavioural difference manifests itself. It remains plausible that many behavioural studies lack statistical power to observe subtle impairments over the entire spectrum of EFs. Therefore, the aim of this meta-analysis was to examine the evidence for overall dysfunction of executive control in ecstasy users compared with polydrug users, but also to examine any functional specific deficits.

Method

Eligibility criteria

Participants

Included studies were those assessing EF in human ecstasy/MDMA users aged 18 years+, who did not have a history of major psychiatric or neurological problems. Ecstasy user groups were eligible if they were described as current ecstasy users; control groups were eligible if they reported some use of drugs, but no ecstasy use – with the exception of studies in which the ecstasy users were recruited with the specific criteria of limited exposure to other drugs. In each case, participants were not intoxicated at the time of testing. The majority of studies included used a minimum abstinence period of 7 days, with the exception of Heffernan et al. (2001), de Sola et al. (2008a ) and Fagundo et al. (2010), who report a minimum abstinence period of 24, 72 and 72 h, respectively. The mean age for ecstasy user group across studies was 23.39 years, with an average of 47.72% females. Mean lifetime dose across studies was 346.03 tablets. The mean age of the control group was 23.11 years, with an average of 54.67% females.

Studies

Studies comparing ecstasy users and controls in performance on behavioural tasks that are function specific were eligible for inclusion. The EFs included in this analysis were: updating; inhibitory control; switching; and access. Tasks eligible for inclusion can be seen in Table 1. There were no date limitations on publication.

Table 1. Tasks included for assessment of each executive function

RT, Reaction time; RLG, random letter generation; ToL, Tower of London; 3D ID-ED, three-dimensional Intra-dimensional/extra-dimensional task; WCST, Wisconsin Card Sorting Test; COWA, Controlled Oral Word Association; CWFT, Chicago Word Fluency Test.

Outcome measures

As each EF can be assessed using several tasks, there are a number of outcome measures. The outcome measure from each task that most clearly taps its putative EF was selected for inclusion in the analysis. As such, each task contributes one outcome measure to the analysis only. Tasks included as well as the outcome measure selected can be seen in Table 1.

Data search and extraction

Information sources and search strategy

The formal search strategy involved searching three electronic databases during July 2015: PsycINFO, Scopus and Web of Science. Systematic searches used the key terms ‘Ecstasy’ OR ‘MDMA’ AND ‘executive function’. Supplementary searches were also conducted using the terms ‘Ecstasy’ and ‘MDMA’ combined with the name of each task in Table 1. Manual searches of reference sections of initially identified studies were conducted to supplement the formal electronic search; furthermore, articles that were not identified in the initial searches that the authors knew to be eligible for inclusion were assessed for inclusion. These additional searches yielded a further five studies eligible for inclusion.

Article selection and extraction of data

Initial searches were carried out by one author (C.A.R.). However, supplementary searches and manual searches were carried out by two authors (C.A.R. and C.M.). Both authors were responsible for the assessment of articles for inclusion, and decisions over article inclusion were made through discussion. One author (C.A.R.) extracted the relevant data and a second author (C.M.) cross-checked this. Several studies met inclusion criteria, but did not report sufficient information in the papers to compute the effect size; in each case data were requested from the corresponding author of the study. Data requests were not met for five articles: Semple et al. (1999); Thomasius et al. (2003); McCann et al. (2007); McCann et al. (2008); and Fagundo et al. (2010).

Additional handling of data

Composite performance scores for letter updating, spatial updating and random letter generation were calculated from the available data, if the composite score itself was not reported in the paper. On occasions where reported values of behavioural performance were split by gender, a weighted mean by number in each sample was calculated. A weighted s.d. was also calculated by multiplying squared s.d.s by number in each group, adding these together, then dividing by total n. The square root of this total was then used as the s.d. in analysis. Data for the FAS task were provided by Morgan et al. (2002), with means and s.d.s given for each letter. Therefore means for performance on each letter were added up to give a total score and the s.d.s were summed and divided by 3.

There were a number of cases where an article had used more than one task to assess an EF (Fox et al. 2001; Gouzoulis-Mayfrank et al. 2003; Montgomery et al. 2005a , 2007; Wareing et al. 2005; Lamers et al. 2006; Montgomery & Fisk, 2008; Fisk & Montgomery, 2009; Halpern et al. 2011). In these cases, means and s.d.s were entered for each task; however, the number of participants in each group was divided by the number of tasks included for that function from that paper.

In de Sola et al. (2008a , b ), between-group comparisons were given 1 year apart. For the meta-analysis, we used baseline measurements of lifetime drug use and task performance. In cases where ecstasy user groups were broken down into further subgroups, e.g. ‘heavy and ‘light’ users (as per Fisk & Montgomery, 2009), data from the heavy user group were included in the analysis. In Fox et al. (2001) the user groups were split into problem/non-problem users and low/medium/high-intensity users. The group of high-intensity users was included in the current analysis. Although the ‘heavy’ and ‘high-intensity’ user group criteria were arbitrarily decided in the original papers, it seemed pertinent to include the user groups with the heaviest background ecstasy use in the current analysis, as these would be the most likely to show ecstasy-related cognitive impairment.

Data items extracted for individual studies

From each of the published papers, the following information was extracted for each group: number of participants; gender split; age; estimated lifetime dose of ecstasy; time since last use; task used (Table 2); outcome measure (Table 1); and means and s.d.s for each outcome variable. In cases where mean ecstasy abstinence duration was not reported, the minimum abstinence period required for the study was recorded. If not reported in the paper, estimates of mean lifetime dose of ecstasy were calculated from the available data. Reported ecstasy user groups could generally be defined by two categories: current users and former users. There were several categories of control groups, including: cannabis-only users; polydrug control groups (who had been recruited due to them having some degree of matching for other substances); non-users (this was a general catch-all name given to controls who were ecstasy naive but did have some other drug use); and drug-naive controls (no illicit substance use, but allowed for use of alcohol and nicotine).

Table 2. Summary of studies included in meta-analysis on executive function in current ecstasy users and drug-using controls ^a

F, Female; MLD, mean lifetime dose; MTSLU, mean time since last use; COWA, Controlled Oral Word Association; MDMA, 3,4-methylenedioxymethamphetamine; ToL, Tower of London task; RLG, random letter generation; WCST, Wisconsin Card Sorting Test; 3D ID-ED, three-dimensional Intra-dimensional/extra-dimensional task; TMT-B, Trail Making Test B; THC, tetrahydrocannabinol; CWFT, Chicago Word Fluency Test.

^a For information on previous exposure to other drugs and other groups not included in the meta-analysis, see online Supplementary Table S1.

Statistical and subgroup analysis

Standardized mean difference (SMD) and standard error (s.e.) of the SMD between experimental conditions were calculated for each executive task outcome separately in each study. SMDs were employed due to variation in outcome measures in the behavioural tasks included in the analysis. SMD estimates differences between two experimental conditions on an outcome variable (SMD = mean1 – mean2/pooled s.d.). This allowed for a subgroup analysis to be conducted by EF (inhibitory control, updating, access and switching). The meta-analysis used generic inverse variance methods to synthesize individual SMDs, in the software package RevMan 5.2 (The Nordic Cochrane Centre, Copenhagen). The magnitude of SMDs can be interpreted thus: 0.2 = small, 0.5 = moderate, and 0.8 = a large effect (Higgins & Green, 2011).

Analytic strategy

The meta-analysis was conducted by separating effect sizes from tasks employed in each study into distinct EFs. The main effect and formal subgroup analysis was examined, whereby each EF was considered a subgroup.

Outcome measures of the various tasks that were included in this meta-analysis had to be reviewed by the authors so that the direction of differences in task performance were consistent for interpretation of ecstasy-related impairment. For example, if ecstasy users produced fewer words on the verbal fluency tasks relative to controls, this would be indicative of ecstasy-related impairment in verbal fluency and would result in a negative SMD in the meta-analysis. However, a greater amount of perseveration errors on the Wisconsin Card Sorting Test would be indicative of impairment yet would yield a positive SMD, should ecstasy users produce more errors here. As such, outcome measures were negatively coded where appropriate.

The main analysis was conducted on the 39 studies that assessed one or more EF in a current ecstasy user group versus a control group that had some use of recreational drugs. Studies that employed a drug-naive control group and no-drug user control group were not included in the analysis, with the exception of three studies (Halpern et al. 2004, 2011; Yip & Lee, 2005). These studies were included, with a drug-naive control group, as their current ecstasy user groups had minimal exposure to other drugs. The remaining studies featured a drug-using control group; as such, all between-group comparisons in this meta-analysis have at least some degree of matching for other drug use. Random-effects models were employed due to high heterogeneity in the data across studies.

Results

Study selection (Fig. 1)

Initial literature searches yielded 99 papers using Web of Science, 79 using Scopus and 386 papers from PsycINFO. After removing 76 duplicated papers, 459 articles remained. A brief review of the remaining article titles and abstracts led to exclusion of 370 irrelevant articles. Excluded papers at this stage included: review articles (23); acute administration studies (26); studies that were conducted using other substances/did not involve ecstasy users (75); studies that were not experimental/did not include behavioural data/assess cognition (232); case studies (8); studies conducted in non-human samples (4); a study not written in English (1); and reanalyses of data (2). This left a total of 88 articles for full review. Further studies were excluded at this stage if they did not employ a function-specific task identified in Table 1 (35), did not employ a control group or current user group, or did not conduct between-group analysis (10). Longitudinal studies using a within-groups design and prospective studies on novice users were also excluded at this stage (4). Following these data exclusion procedures, 39 studies remained. A further five studies eligible for inclusion were identified from supplementary searches. Of the 44 studies that met all the inclusion criteria, data were not available for five; as such, the final meta-analyses were conducted on data from 39 articles (Fig. 1).

Fig. 1. Meta-analysis search results and flow chart.

Overview

Participant characteristics

Individual study information, including sample sizes and participant characteristics, is given in Table 2.

Meta-analysis on EF in ecstasy polydrug users

Data from 39 published studies, contributing 89 effect sizes, were included in analysis, including data from a total of 1221 current ecstasy users and 1242 controls. For descriptive information from each study, see Table 2.

Meta-analyses (Fig. 2)

The test for overall effects was significant [SMD = −0.18, 95% confidence interval (CI) −0.26 to −0.11, Z = 5.05, p < 0.001, I ² = 82%], suggesting an overall executive performance deficit in ecstasy users relative to controls, albeit a small effect. However, there was also a significant subgroup effect (χ² = 22.06, degrees of freedom = 3, p < 0.001, I ² = 86.4%) demonstrating differential effects across EFs. Individual analyses are reported below.

Access

A total of 13 studies, contributing 13 effect sizes, assessed access to long-term/semantic memory, with a total of 483 ecstasy users and 491 controls. A significant difference was observed between these two comparison groups (SMD = −0.33, 95% CI −0.46 to −0.19, Z = 4.72, p < 0.001, I ² = 74%), demonstrating that ecstasy users perform poorly compared with controls in this EF.

Inhibition

A total of 20 studies, contributing 20 effect sizes, investigated performance difference in inhibitory control providing a comparison between 606 ecstasy users and 632 controls. No between-group difference was observed in performance of this EF (SMD = 0.04, 95% CI −0.07 to 0.15, Z = 0.77, p > 0.05).

Switching

Switching was assessed in a total of 488 ecstasy users and 459 controls, in a total of 18 papers, contributing 23 effect sizes. There were significant between-group differences in this function (SMD = −0.19, 95% CI −0.36 to −0.02, Z = 2.16, p < 0.05, I ² = 85%), demonstrating that ecstasy use leads to impairment in mental set switching.

Updating

A total of 872 ecstasy users and 904 controls were compared for updating performance from a total of 24 articles, contributing 33 effect sizes. Again, there was a significant between-group difference in performance of updating tasks (SMD = −0.26, 95% CI −0.37 to −0.15, Z = 4.49, p < 0.001, I ² = 82%). This demonstrates that there is an ecstasy-related impairment with regards to updating performance.

Fig. 2. Forest plot of studies assessing executive function in ecstasy users and drug-using controls. I ² is an indicator of heterogeneity between comparisons. Inverse variance (IV) meta-analysis using standardized (Std.) mean differences. SE, Standard error; CI, confidence interval; df, degrees of freedom.

Meta-regression

We conducted a method of moments (random-effect model) meta-regression across the 64 comparisons included in the main meta-analysis, with the available data for estimates of lifetime dose of ecstasy. This was conducted to observe whether there was a relationship between lifetime dose of ecstasy and SMD in executive performance. The overall meta-regression was non-significant (regression coefficient −0.0001, 95% CI −0.0004 to 0.0002, Z = −0.74, p > 0.05), suggesting that lifetime dose did not predict performance differences. Furthermore, individual meta-regressions performed separately for each specific EF were all non-significant (p > 0.05 in each case).

Evidence of publication bias

Examination of a funnel plot revealed asymmetry; therefore an Egger's test of publication bias was conducted (Egger et al. 1997) on the 89 effect sizes included in this meta-analysis. Egger's test was significant (t ₈₈ = −1.96, p = 0.05), suggesting evidence of publication bias. However, these results should be interpreted with caution due to the high heterogeneity between studies (Sterne et al. 2011).

Discussion

The results from this meta-analysis demonstrate EF deficits in current ecstasy users. However, the size of this overall effect was small. Subgroup analyses showed that effect sizes varied by the specific component of executive functioning. Individual analyses by function showed ecstasy-related deficits in the EFs access, switching and updating, though there was no inhibition performance deficit.

Meta-regression using estimated lifetime dose of ecstasy to predict effect size of between-group differences was non-significant. This suggests that lifetime dose is not the greatest predictor in magnitude of EF deficit. However there were nine studies (providing 25 comparisons) that did not give lifetime estimates of use and so were not included in the analysis, which may have potentially given a different outcome. Nevertheless, there was high variability in effects and although estimates of lifetime use were not possible for all studies, there were 64 comparisons from 30 studies which did include estimated lifetime dose, which is far greater than the minimum of 10 required for adequate power in a meta-regression (Borenstein et al. 2009). Despite adequate power to detect an effect, it could be that the analysis is conceptually flawed, given that it is conducted on SMDs in performance between ecstasy users and controls rather than estimated lifetime dose and task performance (Murphy et al. 2012). Alternatively, it could be that there are other ecstasy-using behaviours that have a stronger impact on behavioural measures, for example recency of use, frequency of use and higher nightly doses. Recency of use has been identified as a predictor of haemodynamic response to a cognitive task in ecstasy users (Roberts & Montgomery, 2015b ). Furthermore, higher nightly doses may make an impact on cognition more than cumulative intake; indeed a single high dose of MDMA is enough to cause neurotoxicity in laboratory animals (Molliver et al. 1990). Unfortunately, there is substantial variance in the reporting of drug use histories in the literature, limiting interpretation. Perhaps some unity on background drug use reporting would vastly improve research and our understanding of harmful behaviours. We propose that a unified reporting criterion should be applied to future research. There are also a number of variables that may contribute to the impact of cumulative dose (Murphy et al. 2012) including earlier onset of use, use of other drugs, and increased bioenergetic stress (Parrott, 2009).

Neuronal regions implicated in working memory and EF include the DLPFC and the hippocampus (depending on the nature of the task). These structures have dense innervation of serotonergic (5-HT) neurons (Pazos et al. 1987; Curtis & D'Esposito, 2003). Therefore ecstasy-related degradation to the serotonin system, through neurotoxicity or down-regulation following chronic recent use, is understood to be a potential cause of cognitive impairment in the functions supported by these areas. If ecstasy is a serotonin-specific neurotoxin in humans as it is in animals (Green et al. 2003), one would expect functional alterations following repeated use. Several molecular imaging studies in human ecstasy users suggest a reduction in pre-synaptic serotonin transporter (SERT) availability in areas including the frontal cortex (McCann et al. 1998; Kish et al. 2010) and the DLPFC (McCann et al. 2005). Increases in post-synaptic 5-HT_2A receptors have also been observed in ecstasy users relative to controls in the DLPFC (Urban et al. 2012). Decreased pre-synaptic SERT and increased post-synaptic 5-HT_2A receptor availability are consistent with serotonin axon damage. Moreover, functional neuroimaging studies have observed ecstasy-related adjustments to cerebral blood flow in frontal areas, with functional near-infrared spectroscopy (Roberts & Montgomery, 2015a ) and fMRI (Moeller et al. 2004; Jager et al. 2008; Roberts & Garavan, 2010). It is noteworthy that all of the functional imaging studies mentioned observe increased neuronal activity to achieve similar behavioural performance to controls. This suggests that molecular and functional neuroimaging detect changes in serotonin signalling which cause future deficits in EF. The current results support this by demonstrating behavioural correlates for the supposed neuronal degradation.

Ecstasy-related impairments in switching were unexpected, given that previous reviews in this area have concluded that this function is relatively stable (Murphy et al. 2009). However, some studies have observed significant switching differences between ecstasy users and controls (Halpern et al. 2004; Dafters, 2006a ) and neuroimaging studies have suggested atypical processing during switching (Roberts et al. 2013c ). This highlights the necessity for larger samples to elucidate this performance deficit. However, this difference was the weakest of the three significant differences and had a small effect size; thus it should be treated with caution. The reduced performance in updating and access in ecstasy users relative to controls is more consistent with previous reports (Montgomery et al. 2005a ; Murphy et al. 2009). Nevertheless, there have been previous reports of null findings in these functions. The ability to update one's memory is reflective of the concept of working memory as a whole, and Miyake and co-workers (Friedman et al. 2006; Miyake & Friedman, 2012) maintain that updating is the key overarching EF which is important for daily function.

Although not unexpected, it is interesting to consider why there were no apparent group differences in inhibitory control. One explanation could be that ecstasy users are high-functioning impulsives and this increased impulsivity serves to mask performance deficits on the tasks employed here (Fritzsche et al. 2011). Alternatively, perhaps inhibitory control impairment is associated with other psychostimulants that are primarily dopaminergic in nature, e.g. cocaine (Fillmore & Rush, 2002) and methamphetamine (Monterosso et al. 2005). Interestingly, in recent models of the unity and diversity of EFs, Miyake & Friedman (2012) confer that inhibitory control is not necessarily a unique EF. Instead, inhibitory control is subsumed by common EF ability. With this in mind, it could be suggested that ecstasy users are therefore impaired at each level of EF.

There are a number of limitations of the current analysis. Concomitant use of other drugs is often posited to contribute to the cognitive deficits displayed by ecstasy users. To try and incorporate this into the meta-analysis, comparisons were made between ecstasy users and controls that have at least some experience with drugs other than ecstasy. Nevertheless, it should be noted that in many of the studies in the analysis, the use of drugs other than ecstasy was, in fact, higher in the ecstasy user groups than the polydrug control groups (in terms of total lifetime dose, frequency of use and variety of drugs used). As such, we cannot rule out the possibility that alcohol and other drugs may also contribute to deficits in executive functioning. However, despite the increased polydrug use among ecstasy user groups, there are several instances of drug use indices predicting unique variance in EFs in regression analyses (for example, Schilt et al. 2008); this suggests that various chronic drug effects do show independence from one another. Increased cohesion in reporting of drug use variables would help to remove some of this uncertainty in future. Similarly, it cannot be ruled out that the direction of causality is interpreted incorrectly. It could be that individuals with EF deficits are more likely to have a stronger propensity for ecstasy use, though the authors think that this is unlikely. Future research should concentrate on longitudinal studies to obviate confusion over direction of causality. Furthermore, as the current analysis is conducted on current users and therefore cannot make any predictions about function recovery following abstention, longitudinal studies may also help to determine whether recovery is possible. The current results suggest that ecstasy users may struggle with higher-level executive functioning, and it has been suggested that such impairments would lead to difficulty in performing the majority of occupational tasks (Parrott, 2013a , b ). Montgomery et al. (2010) observed ecstasy users to be impaired at a virtual reality office work task, with the suggestion that office work, as well as those occupations requiring greater executive resources, will be adversely affected by ecstasy use. Taken together, these findings suggest that prolonged ecstasy use can lead to everyday functioning problems; therefore an understanding of the processes underpinning such impairments may prove valuable to clinicians.

To conclude, the current meta-analysis demonstrated that EF performance in ecstasy users is significantly reduced overall compared with controls. The three functions that show significant impairment are updating, switching and access, whilst inhibitory control is unaffected by ecstasy use. This is the most comprehensive analysis of EF in ecstasy users to date and provides a behavioural correlate of potential serotonergic neurotoxicity.