How to avoid the fallacies of cognitive subtraction in brain imaging

Functional neuroanatomy of cognitive processes is generally derived by subtraction of a control task from an experimental task. We show that this method is logically untenable and propose to replace it with an adaptation of the specific-effect method and of the additive-factor method. The basic flaw that undermines the subtractive method is the comparison between different tasks. We argue that the specific-effect method should be used when investigating activations produced by different levels of a qualitative variable, whereas the additive-factor method should be used for quantitative variables. The use of these methods allows one to distinguish between parallel and serial stages of processing and between local and distributed processing.     

Response coding and visuomotor transformation in the Simon task: the role of action goals

Manual responses can be defined by differing response parameters. Any of them may generate a Simon effect. For all those response parameters, the same implementation of the Simon effect (in terms of subserving mechanism) is assumed. In 3 experiments, subjects had to respond with either fingers or sticks. Temporal properties of the Simon effect changed with response parameters relevant in a task. The Simon effect for manual responses decayed. For stick responses, in which the action goal differed from the anatomical mapping of the acting hand, a sustained Simon effect was observed. However, if the action goal for stick responses was not instrumental for selecting the correct response, the Simon effect decayed. The findings are consistent with the notion of different mechanisms involved in generating a Simon effect.     

Cross-dimension-ambivalent in-group stereotypes: the moderating roles of social context of stereotype endorsement and in-group identification

In this study, the authors examined in-group stereotypes that are cross-dimensionally ambivalent-simultaneously (a) positive in cognition-related content dimensions and negative in affect-related content dimensions or (b) negative in cognition-related content dimensions and positive in affect-related content dimensions-to establish whether endorsement of such in-group stereotypes depends on whether this process occurs in an intragroup versus intergroup context. Drawing on social identity theory, the authors predicted that (a) endorsement of cross-dimension-ambivalent in-group stereotypes would be greater in an intragroup, relative to an intergroup, context and (b) this would hold for high but not low in-group identifiers. Confirming these hypotheses, results showed that endorsement of cross-dimension-ambivalent in-group stereotypes may vary as a function of their contribution to securing a positive social identity.     

Psychometric properties of the Spanish version of the Frost Multidimensional Perfectionism Scale in women

This instrumental study was designed to analyze the psychometric properties of the Spanish version of the Frost Multidimensional Perfectionism Scale (FMPS). The total sample was made up of 582 female college students, with a mean age of 21.68 (SD= 4.45). The results of confirmatory factor analysis identified the six-factor solution proposed by the original authors as the best factor structure, with acceptable fit indices. Cronbach's alpha coefficient was .93 for the FMPS total score and ranged from .74 to .91 for the subscales. Test-retest reliability suggested a good temporal stability of the FMPS total score [ICC= .89 (95% CI= .80-.94)] and its subscales. Results showed moderate to high associations between the Spanish version of the FMPS and other measures of perfectionism. The Spanish version of FMPS has shown satisfactory psychometric properties to be used in women. Future research should replicate these findings in broader samples, in clinical populations, and use longitudinal designs to determine whether perfectionism is a risk factor for psychopathology in women.     

Testing the Relationship Between Parents’ and Their Children’s Subjective Well-Being

Casas et al. (J Happiness Stud 9(2):197–205, 2008) found no significant relationship between paired answers given by parents and their 12–16-year-old children (N?=?266) for a single-item scale on overall life satisfaction (OLS). However, a significant, but low (.19) parent–child relationship did appear for the PWI multi-item scale. Overall, children reported higher subjective well being than parents. In this article, we present the results obtained from confirmatory factor analysis (CFA), using more scales and a bigger sample (N?=?1,250) of paired parents and children. The study uses three multiple-item scales: the PWI, the SWLS and the BMSLSS, and six single-item scales: the OLS, two items from Russell’s scale on core affects, one on overall happiness, Fordyce’s happiness item and the optional item of the BMSLSS on overall life satisfaction. Separate CFA for each of the 3 multi-item scales showed good fit statistics. In order to check comparability between parents and children, we tested equal loading and intercept constraints. The models with restricted loadings fit only for the PWI and BMSLSS, but none of the models with restricted intercepts fit. Therefore, it was only possible to estimate two factor correlations for parents and their children, both very low (.16 for the PWI, .18 for BMSLSS), and it was not possible to compare factor means. When correlating scores from the 6 single-item scales for parents and children, they were all found to be significant but very low. As regards items from the multiple-item scales for parents and children many correlations are positive and significant, although very low, but others are non significant. The means of some items were substantially higher for children than for parents. For some items, differences were minor, non-significant or even reversed. All of the results suggest that parents’ well-being is very weakly related to their own children’s well-being, in spite of socialization, common material welfare and genetic influences. However, one outstanding result is that in our Catalan sample, parents’ well-being seems to have a greater influence on their female child’s well-being than on their male child’s.     

The Contribution of Job Happiness and Job Meaning to the Well-Being of Workers from Thriving and Failing Companies

In a time of global economic crisis, workers’ well-being is of paramount concern for both organizations and society at large. Conceptualizations within positive psychology distinguish between hedonic and eudaimonic well-being components, and call for the need to include them in an integrated perspective. Within this framework, the present study aimed at investigating the impact of situational uncertainty on eudaimonic and hedonic well-being, and the spillover effects of work into individuals’ lives. Data were collected from 85 Italian employees at a thriving insurance company and at a failing one. Participants were administered Job Content Questionnaire, Eudaimonic and Hedonic Happiness Investigation, Satisfaction with Life Scale, and Psychological Wellbeing Scales. Data were analyzed through hierarchical regression analyses. Concerning well-being at work, employees at the failing company reported higher job insecurity and lower job happiness compared to employees at the thriving company, while job meaning scores did not differ between groups. Concerning general well-being, an unexpected positive association was found between positive relations and situational uncertainty. A spillover effect of job happiness and meaning on life satisfaction, environmental mastery, and autonomy was also detected. In particular, a moderating effect of job meaning was identified, showing that attributing high importance to one’s job had wide affective consequences, spilling over to global life evaluations. Findings bring forward practical suggestions for well-being promotion, in terms of shifting domain importance (Wu Journal of Happiness Studies 10:37–47, 2009), and investing in multiple life areas (Sirgy and Wu Journal of Happiness Studies 10:183–196, 2009) for the promotion of a balanced life.