Despite the fact that literature regarding the implications of envy in the work environment has generated growing interest in recent years, the role of malicious and benign envy in the workplace has scarcely been studied. Therefore, the present study, using an experimental design, N = 213 (140 female and 73 male; Mage = 31.05, SD = 10.01; range from 18 to 68), aims to examine the effects of malicious (vs. benign) envy on perceived injustice, negative emotions, and the individual tendency to express counterproductive work behaviors. The results obtained showed that the mere activation of malicious envy (vs. benign envy) leads to an increased perceived injustice (p < .001, ηp2= .15), and to higher levels of negative emotions (p < .001, ηp2= .18) and counterproductive (harmful) behaviors toward the envied co-worker (p < .001, ηp2= .16). Additionally, we found that perceptions of injustice and negative emotions mediated the effect of malicious (vs. benign) envy on the inclination to express counterproductive work behaviors (Indirect Effect (IE) = .227, SE = .064, 95% CI [.127, .386]. Finally, these findings and their possible implications are discussed.

In the present study, we conducted two experiments (Experiment 1: 35 participants, M = 29; SD = 8.4; Experiment 2: 36 participants, M = 25; SD = 6.1) with the intention to explore whether underlying perceptual grouping operations and illusory form perception generate dissociable priming effects when Kanizsa-like figures are presented as primes and the rotated inducers as controls under conditions of restricted awareness. Using five different stimulus onset asynchronies (SOA conditions, Experiment 1: 27, 40 and 53 ms; Experiment 2: 27, 80 and 227 ms), we displayed masked illusory and groping primes that could be congruent or incongruent in their orientation with subsequent probe stimuli (vertical vs. horizontal). We found significant priming effects in both Experiment 1 and 2 (p < .001, η2p = .31 and p = .016, η2p = .16, respectively), but, crucially, no significant priming differences between illusory and grouping primes across SOA conditions. Overall, our results are important in showing that a dissociation of the percept generated by the grouping of the inducers from that generated by the illusory form is crucial in the study of illusory form perception under conditions of restricted awareness. In addition, they provide further evidence of perceptual organization operations occurring under very restrictive awareness conditions.

The objectives of this study were to replicate the analyses conducted by the creators of the Indicators of Abuse (IOA) Screen with a Spanish sample group and compare the results, to present new validity evidences, to analyze which items were more relevant in the detection of situations of risk of abuse, and to establish a cut-off point to interpret the obtained scores. The IOA was used by 46 professionals from social services teams who assessed the situation of 231 elderly individuals and their main caregivers. The obtained results advocated towards unidimensionality of the scale. It showed a high level of internal consistency (α = .94). The Confidence Interval of 99% for the alpha coefficient was between .92 and .95. The ordinal alpha coefficient reached the value of .98. The total score of the scale showed adequate temporal stability (r = .91; p ≤ .001; N = 163). Statistically significant differences (t-test) in the mean scores of most of the items were found between cases of adequate treatment and cases of risk of abuse. The scale classified correctly 93% of all cases. The best balance between sensitivity and specificity was found at the cut-off point given by score 16 (Sensitivity = 0.94, Specificity = 0.85). The results appear to confirm the validity evidence of the instrument when used with a Spanish population. However, it is necessary to conduct further research and confirm the results with wider, more representative sample groups.

This study aimed to propose an adapted feedback using a psychological learning technique based on Skinner’s shaping method to help the users to modulate two cognitive tasks (right-hand motor imagination and relaxed state) and improve better control in a Brain-Computer Interface. In the first experiment, a comparative study between performance in standard feedback (N = 9) and shaping method (N = 10) was conducted. The NASA Task Load Index questionnaire was applied to measure the user’s workload. In the second experiment, a single case study was performed (N = 5) to verify the continuous learning by the shaping method. The first experiment showed significant interaction effect between sessions and group (F(1, 17) = 5.565; p = .031) which the shaping paradigm was applied. A second interaction effect demonstrates a higher performance increase in the relax state task with shaping procedure (F(1, 17) = 5. 038; p = .038). In NASA-TXL an interaction effect was obtained between the group and the cognitive task in Mental Demand (F(1, 17) = 6, 809; p = .018), Performance (F(1, 17) = 5, 725; p = .029), and Frustration (F(1, 17) = 9, 735; p = .006), no significance was found in Effort. In the second experiment, a trial-by-trial analysis shows an ascendant trend learning curve for the cognitive task with the lowest initial acquisition (relax state). The results suggest the effectiveness of the shaping procedure to modulate brain rhythms, improving mainly the cognitive task with greater initial difficulty and provide better interaction perception.

The Spanish term grima refers to the aversive emotional experience typically evoked when one hears, for example, a scratch upon a chalkboard. Whereas Spanish speakers can distinguish between the concepts of grima and disgust, English and German speakers lack a specific word for this experience and typically label grima as disgust. In the present research, we tested the degree of differentiation between the two aversive experiences in Spanish speakers. Study 1 addressed whether Spanish speakers apply spontaneously the term grima rather than disgust to grima-eliciting experiences. Study 2 systematically addressed the constitutive features of both grima and disgust by mapping their internal structures. Results showed that the noise of a chulk on a blackboard and scraping fingernails on a blackboard, along with the physical manifestation of goose bumps, were the most typical features of the category. Whereas both grima and disgust were characterized as unpleasant sensations, t(193) = 1.21, ns, they differed with respect to their physiological signatures (e.g., producing shivers was characteristic of grima, as compared to disgust, t(194) = 12.02, p = .001, d = 1.72) and elicitors (e.g., a fractured bone was a characteristic elicitor of grima; t(193) = 5.78, p = .001, d = .83, whereas pederasts and pedophiles were the most characteristic elicitor of disgust, t(193) = 8.46, p = .001, d = 1.21). Thus, both grima and disgust are conceptually different experiences, whose shared features hold different degrees of typicality. The present research suggests that grima and disgust are two distinct emotion concepts.

Motivation and coping are two of the most relevant factors associated to well-being. One of our objectives was to describe the motivation to pursue the personal goals, the coping strategies used to pursue them, and the levels of well-being experienced, in a group of people serving prison sentences (n = 175: 143 males and 32 females). We mainly wanted to study the joint contribution of motivation and coping on their well-being. The results have shown that motivation and coping contribute to the different dimensions of well-being. Specifically, we have found that autonomous motivation (AM) as well as problem solving (PS) and positive cognitive restructuring (PCR) coping positively predict self-acceptance (β = .12, p = .06; β = .17, p < .05; β = .24, p < .01 respectively), purpose in life (β = .12, p = .06; β = .35, p < .001 and β = .24, p < .001 respectively) and positive affect (β = .13, p = .06; β = .29, p < .001 and β = .28, p < .001 respectively). Personal growth was positively predicted by AM (β = .21, p < .01) and PCR coping (β = .21, p < .01), and negatively by avoidance coping (β = –.16, p < .05). Negative affect was positively predicted by social support (β = .16, p < .05) and avoidance (β = .42, p < .001) coping. None of the variables analyzed predicted life satisfaction. The results suggest that well-being promotion programs in prison settings should encourage the pursuit of goals by AM and the use of PS and PCR coping to achieve these goals.

From a dispositional perspective, we extend the action identification theory (Vallacher & Wegner, 1987) and construal level theory (Trope & Liberman, 2003) to cross-situational consistency of self and self-control. Two studies examined the relationships among the abstract mindset (Vallacher & Wegner, 1989), cross-situational consistency in self-concept (Vignoles et al., 2016), and self-control (Tangney, Baumeister, and Boone 2004). In Study 1, participants (N = 725) characterized by high cross-situational consistency showed more abstraction in their thinking (p < .001, ηp2 = .17). In Study 2 (N = 244) cross-situational consistency and self-control explained 10% of construal level, with self-control being a significant predictor (p < .001). Construal level and cross-situational consistency explained 17% of self-control; both were significant predictors (p < .001). Self-control explained 8% of cross-situational consistency (p < .001). Study 2 showed that participants with higher levels of abstraction, cross-situational consistency, and self-control reported a greater intention to control their future sugar intake (p < .001). Data supported relationships among abstract construal level, cross-situational consistency and self-control.

Bullying and cyberbullying pose a serious problem in our schools. Despite this research area’s increasing relevance, most research into cyberbullying in the present day has focused only on adolescents. However, given the long-lasting effects of victimization, it is necessary to understand its prevalence throughout the different educational stages of students. This study aims to clarify the prevalence of bullying and cyberbullying among students in the 5th and 6th grades. A sample of 1,993 (Mage = 10.68, SD = 0.71; range 9–13) students completed the “Cyberbullying: Screening of Peer-Harassment” test. The results reveal that 20.3% (n = 404) were pure victims, 6.1% (n = 121) pure bullies, 23.9% (n = 476) bully-victims, and 28.9% (n = 575) pure bystanders of bullying. With respect to cyberbullying, 13.4% (n = 267) were pure cybervictims, 0.7% (n = 13) pure cyberbullies, 3.1% cyberbully-victims (n = 62), and 25.6% (n = 510) pure cyberbystanders. In addition, the results reveal that verbal aggression and offensive or insulting messages were the most prevalent forms of aggression in bullying and cyberbullying, respectively. 36.6% of the sample had suffered verbal aggression and 8.4% had received offending or insulting messages. These data show that bullying and cyberbullying are considerably prevalent in this educational stage.

The present experiment examined how the interaction between senders’ communicative competence, veracity and the medium through which judgments were made affected observers’ accuracy. Stimuli were obtained from a previous study. Observers (N = 220) judged the truthfulness of statements provided by a good truth teller, a good liar, a bad truth teller, and a bad liar presented either via an audio-only, video-only, audio-video, or transcript format. Log-linear analyses showed that the data were best explained via the saturated model, therefore indicating that all the four variables interacted, G2(0) = 0, p = 1, Q2 = 1. Follow-up analyses showed that the good liar and bad liar were best evaluated via the transcript (z = 2.5) and the audio-only medium (z = 3.9), respectively. Both the good truth teller and the bad truth teller were best assessed through the audio-video medium (z = 2.1, good truth teller, z = 3.4, bad truth teller). Results indicated that all the factors interacted and played a joint role on observers’ accuracy. Difficulties and suggestions for choosing the right medium are presented.

A high percentage of patients have a diagnosis of adjustment disorder (AD) when they arrive at primary care (PC) appointments. However, most of them do not receive adequate psychological treatment. The present study’s aim is to determine the efficacy of a group psychological treatment program in patients with AD. The sample consisted of patients with AD from two PC units in Valencia, from which two groups were randomly generated: A treatment group (n = 31) and a waiting-list group (n = 20), homogeneous in terms of socio-demographic and psychometric variables prior to treatment. Treatment consisted of eight one-hour group sessions held on a weekly basis; taking a cognitive-behavioral approach, they addressed aspects like controlling anxiety, cognitive restructuring, and coping techniques. The variables analyzed were: Psychopathology (Revised Symptom Inventory, SCL–90–R), health-related quality of life (Health Questionnaire, SF–12), and risk of suicidal behavior (Suicide Risk Scale). Means comparisons, ANCOVAs, and tests of effect size were performed. Statistically significant differences were observed in the variables, such that after intervention, the experimental group exhibited less anxious (F = 4.11, p =.048, η2 = .08) and depressive symptoms (F = 2.41, p =.029, η 2= .10) and higher quality of life related to physical (F = 7.17, p =.010, η2 = .13) and emotional health (F = 10.31, p =.002, η2 = .18). For the reasons above, we conclude that a comprehensive approach to emotional distress in PC, including group psychological interventions, is one solution for the demand for social services, and could provide savings on economic as well as human costs.

Applications of job crafting are widespread in the professional practice. In an attempt to measure this phenomenon, Tims, Bakker and Derks (2012) developed a Job Crafting Scale based on the Job Demand-Resources model (JD-R) and validated it in a Dutch sample. However, its application to other cultural contexts presented some difficulties. The present work aimed to validate a shorter version of scale by Tims et al. (2012) in a Spanish sample (n = 1,647). The data were randomly split in two independent subsamples (Sample 1: Explorative; Sample 2: Confirmative). The exploratory factor analysis showed a three-factor structure. Through a confirmatory factor analysis, the four-dimensionality structure of the original scale was replicated. In fact, the four-factor solution presented better goodness of fit indices than the alternative one-factor model, χ2(48) = 192.70, p < .01; AGFI = .94; NNFI = .93; RMR = .05; RMSEA = .06. Alpha reliabilities were acceptable for increasing structural job resources (α = .75), decreasing hindering job demands (α = .64), increasing social job resources (α = .78) and increasing challenging job demands (α = .77). Convergent validity was appropriate for three of the four dimensions, because each construct’s AVE were around .50 and each construct’s Composite Reliability were around .70. Decreasing hindering job demands presented more limited values (CR = .65; AVE = .40). In addition, the four job crafting dimensions presented significant correlations with job performance (range –.09 to .42) and personal growth (ranging from –.09 to .45). Finally, the squared correlations between factors were lower than the square root of AVE, which confirmed discriminant validity.

One of the most relevant phenomena both from a theoretical and clinical perspective is extinction. In particular, several researchers are interested in the response recovery effects from extinction. Reinstatement is an effect that has been proposed as a laboratory model to study relapse from extinction-based therapeutic treatments. We designed two experiments with humans to evaluate the reinstatement effect in a predictive learning task. In both experiments, participants learned a specific relationship between two cues (X and Y) and two outcomes (O1 and O2) during the first phase. Throughout extinction, both cues were presented without outcomes. After an exposure to the original outcomes, reinstatement of the first-learned information was observed during testing in both experiments. However, we found that the reinstatement effect was contextual modulated (Experiment 1; ηp2 = .78, 90% CI [.48, .86], p < .0001). Furthermore, in Experiment 2 we showed a reduction of reinstatement when an extinction reminder was used ηp2 = .45, 90% CI [.07, .65], p = .012. Theoretical implications are discussed, and some potential uses are mentioned.

The Gratitude Questionnaire is a short, self-report measure of the disposition to experience gratitude. The Gratitude Questionnaire has been validated in several countries but its factor structure remains controversial. Therefore, the main goal of the study was to examine the factor structure of the Gratitude Questionnaire in a Spanish sample. Two samples were recruited (957 and 920 participants). The confirmatory factor analyses showed that the best fit was the five-item model with errors of item four and five correlated (CFI = .99, NFI = .99, RMSEA = .02). This model demonstrated partial cross-validity based on an analysis of factorial invariance. The Composite Reliability of the five-item Gratitude Questionnaire was .81. In addition, it was found that gratitude was positively related to subjective and psychological well-being. Specifically, the Gratitude Questionnaire was positively correlated to life satisfaction (r = .56, p < .01), affect balance (r = .46, p < .01), self-acceptance (r = .54, p < .01), positive relations (r = .44, p < .01), autonomy (r = .17, p < .01), environmental mastery (r = .49, p < .01), personal growth (r = .36, p < .01), and purpose in life (r = .50, p < .01). According to the results, it can be concluded that the Spanish version of the five-item Gratitude Questionnaire possessed better psychometric properties than the original six-item model.

In this study, we examined coping strategies as a mediator of the association between loneliness and depressive symptoms. A sample of 364 Spanish young adults (75.5% females) completed measures of loneliness, coping, and depressive symptoms. In general, results from computing correlations (controlling for gender) indicated that loneliness was negatively associated with the use of one engaged coping strategy (viz., problem solving) and positively associated with the use of disengaged coping strategies (e.g., problem avoidance). A multiple mediation analysis (controlling for gender) was conducted to test for mediation. Results of this analysis indicated that part of the association between loneliness and depressive symptoms can be explained by the use of one engaged coping strategy (viz., problem solving; indirect effect, p < .05) and a variety of disengaged coping strategies (viz., problem avoidance, wishful thinking, social withdrawal, & self criticism; indirect effects, p < .05). Overall, the prediction model including loneliness and coping strategies was found to account for a large (f2 = .68) 40.5% of the variance in depressive symptoms in Spanish young adults. The present findings are the first to clarify how the association between loneliness and depressive symptoms in Spanish young adults might be due in part to the use of different coping strategies. Some implications for theory and practice are discussed.

We studied memory of health scenarios for end-of-life support decisions and stability of life support preferences. Psychology students (n = 36, age M = 27.25, SD = 6.21, 64% females) were administered the Life Support Preferences Questionnaire to assess their memory of six medical scenarios with different prognoses, care treatment, and end-of-life support choices. Recall, recognition, confidence and decision stability were assessed immediately and one month later. Correct recall decreased and incorrect recall increased from immediate to long-term recall, F(2, 68) = 74.38, p < .001, η2p = .69. In recall, participants spontaneously gave false information consistent with prior knowledge of illnesses and medical scenarios. Participants who had suffered a disease or serious accident did worse on correct recall, F(1, 34) = 6.59, p = .015, η2p = .16, and had more errors, F(1, 34) = 4.68, p = .038, η2p = .12, than participants who had not. In the recognition test there were no differences between hits and false alarms, showing the difficulty in discriminating between true and false contents. Confidence was greater for hits than for false alarms, F(1, 34) = 10.86, p = .002, η2p = .24, but this subjective measure did not seem to be a good predictor of accuracy because confidence was greater than the mean value for hits (p = .001, d = 1.74) and for false alarms (p = .001, d = 0.96). Long-term memory was quite poor and biased, but life support preferences did not change much.

The purpose was to assess the psychometric properties of the French version of the Young Schema Questionnaire - Short Form 3 (YSQ–S3). The main non-clinical sample (N = 605, M = 20.63, 78% women) was divided into two subsamples: One was used for exploratory factor analyses (EFA) and the other was used for confirmatory analyses. Next, internal consistency, convergent validity and criterion-related validity were studied. The EFA to each of the five domains was similar to the theoretical structure postulated by Young. The confirmatory analysis of each of the five domains appeared to favor our solution over a single-factor solution and Young’s solution. The confirmatory factor analyses of high-order structures did not give fully satisfactory results but appeared to favor our solution (RMSEA =.11, CFI =.76, TLI =.71, SRMR =.07, AIC = 58,566.44). In our best model, the reliability (> .70) was satisfactory for fourteen schemas. The relationships between the schemas and the neuroticism, extraversion and psychoticism scores went in the expected directions. Detrimental parental rearing behaviors were linked to high scores for the various schemas. Lastly, 4 schemas differentiated between the clinical and non-clinical groups. In conclusion, the overall psychometric qualities of the French version of the YSQ–S3 allow its use in clinical populations.

Personality characteristics such as extraversion, low agreeableness and low conscientiousness are relevant for alcohol use during adolescence. In addition, having friends who use alcohol is one of the strongest predictors of adolescent alcohol consumption and its negative outcomes. The selection model posits that friends display similar alcohol consumption when their friendships are formed on the basis of common characteristics as, among others, personality. Thus, the aim of this study was to examine the mediation role of peers in the association between the five-factor model of personality and adolescent alcohol use in two cultures. One hundred and twenty Scottish and 221 Spanish respondents, all aged 12-15 years, answered the Alcohol Intake Scale (AIS). Adolescents were asked about the alcohol used at the weekend and also about the alcohol consumed by their friends. Scottish adolescents’ personality was measured by the NEO Personality Inventory-3 (NEO–PI–3). The Junior Spanish version of the Revised NEO Personality Inventory (JS NEO) was used to assess personality in the Spanish sample. Low agreeableness and low conscientiousness correlated with own alcohol quantity in both countries. We performed an independent structural equation modeling for each country. Extraversion (β = .205, p < .05) and low agreeableness (β = –.196, p < .01) for Scottish adolescents, and low conscientiousness (β = –.175, p < .05) for Spanish youths, predicted alcohol use through peer alcohol consumption at weekends. These findings support the relevance of personality traits and peer affiliation in relation to alcohol consumption in adolescence.

Parents are the first to indicate concerns about their child’s development in up to 80% of children with autism spectrum disorder (ASD). They often notice symptoms related to ASD around the first two years, but the average age of diagnosis is 3.5 years old. This study examined the relationships between parents’ early concerns and the time lag between suspicion and diagnosis. Forty-eight Spanish-speaking families were enrolled in this study. Parents were asked about early signs that made them think that their child could possibly have ASD. Mediation analyses showed that the child’s age at suspicion mediated between sibling status and the time lag between suspicion and a formal diagnosis (β = –.53, p < .01). Having another child with typical development accelerated parents’ detection of ASD signs (β = –.62, p < .001). The number of social-communication concerns that parents detected mediated this relationship (β = –.28, p < .01). Parents who reported more social-communication concerns perceived these signs earlier, but have to cope with a longer time lag until diagnosis than those who reported more concerns related to restrictive and repetitive behaviors and interests, or other developmental concerns. Moreover, this relationship between concerns of ASD and the diagnoses was explained by the child’s age. Training pediatricians on how to respond to parent questions and concerns could reduce the time lag between parents’ concerns and diagnosis of ASD.

The Bipolar Spectrum Diagnostic Scale (BSDS) is widely validated and used as a screening tool for bipolar disorder. However, there is no BSDS validated version for its use in Mexican population. The aim of the present study was to examine the BSDS diagnostic capacity, and to evaluate its criterion validity and internal consistency for its use in Mexican psychiatric patients. We recruited 200 patients who attended the psychiatric outpatient service of a Mental Health Specialized Hospital and were screened for bipolar disorder using BSDS. To determine the cut-off point, sensitivity and specificity, we used the SCID–I diagnosis as the gold standard in 100 participants with bipolar disorder and 100 with major depression. Internal consistency according to Cronbach’s coefficient alpha was .81. The area under ROC curve for the overall discriminability of BSDS against the criterion of SCID–I for bipolar disorder was .90. Finally, a cut-off value of 12 reached the most stable sensitivity and specificity, with predictive powers higher than .80. In conclusion, the properties of the scale including internal consistency, sensitivity and specificity, make of BSDS a valuable instrument for screening bipolar disorder in Mexican psychiatric population.