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Working memory, negative affect and personal assets: How do they relate to mathematics and reading literacy?

Working memory, negative affect and personal assets: How do they relate to mathematics and reading literacy?

  • Enrica Donolato, 
  • David Giofrè, 
  • Irene C. Mammarella



Research has recently focused on the relationships between working memory, negative affect (e.g., general anxiety, depressive symptoms) and personal assets (e.g., self-concept, academic and competence dimensions, and ego-resiliency), and their influence on mathematics and reading literacy. Although these variables have been amply explored, previous research has usually considered each of these aspects in isolation.


In the present study, 143 schoolchildren in sixth to eighth grade were tested on general anxiety, depressive symptoms, working memory, self-concept (academic and competence scales), ego-resiliency, and mathematics and reading literacy.


Variance partitioning showed that all predictors, i.e., working memory, negative affect (i.e., general anxiety and depressive symptoms), and personal assets (i.e., self-concept, academic and competence dimensions, and ego-resiliency) explained a unique and shared portion of the variance in mathematics and reading literacy.


Our findings point to the importance of investigating the relationship between these factors. Underlying implications and directions for future research are discussed.


Academic success is a key aspect of a child’s life and development. Schoolchildren are required to achieve goals that are of fundamental importance to their future employment, income, and health status in adult life [13]. A great deal of literature has focused on various aspects relating to educational and developmental outcomes. For example, several studies examined individual factors related to academic success, such as motivation [46], implicit theories [7,8], goal-directed effort [9], and academic emotions [10,11]. Among such factors, general anxiety and depressive symptoms (called ‘negative affect’ from here on) were found to be associated with lower academic achievement [12,13]. On the other hand, self-concept and ego-resiliency (called personal assets from here on) seem to support children in their academic life [1416]. Previous research also showed that working memory (WM) is one of the most important factors involved in academic achievement [1719]. Research has yet to consider the unique contribution of all these variables to school-aged children’s academic performance, however. To fill this gap, the present study aims to examine the unique and shared contribution of negative affect, personal assets and WM in two key academic domains relating to mathematics and reading literacy.

Negative affect, personal assets and academic achievement

The effects of general anxiety and depressive symptoms on academic achievement have been widely investigated. General anxiety can be defined as an individual's tendency to feel anxious about everyday situations, which may involve physiological anxiety, worry and social anxiety [20,21]. Depressive symptoms refer to low mood, intrusive ruminative thoughts, loss of interest and social withdrawal [22,23]. Current research on the prevalence of these emotional problems suggests that approximately 2.5% to 5% of children and adolescents meet the criteria for an anxiety disorder at some point [2427], and that 2.8% to 8% of children and adolescents suffer from a depressive disorder [28,29]. As for the relationship between general anxiety and depressive symptoms, these two aspects frequently co-occur in childhood [30], and individuals suffering from these emotional problems often experience academic difficulties such as lower grades and graduation rates [13,3133]. A recent meta-analysis confirmed that general anxiety and depressive symptoms tend to be negatively associated with school attainment [12]. It should be noted, however, that most of the previous research focused on clinical samples, while the few studies on typically-developing children produced inconsistent findings [34,35].

Alongside general anxiety and depressive symptoms, other factors related to school attainment include personal assets, for instance. Personal assets are features that help children to foster competence and promote their successful development in the personal, social and academic domains [36,37]. Among the various personal assets, self-concept and ego-resiliency can support children in different aspects of everyday life, including their academic performance [3840]. Self-concept can be defined as a multidimensional and context-dependent learned behavioral pattern, based on personal assessments of one’s own past behavior and experiences, that influence an individual’s present and future behavior [41]. Ego-resiliency can be defined as a set of personal characteristics that help an individual to adapt to the environment, and recover quickly from everyday life challenges and difficulties [42,43]. A more comprehensive elaboration of the ego-resiliency construct suggests that ego-resilient people can show general resourcefulness, strength of character, and flexibility of functioning that enable them to adapt to, and recover from internal and environmental stressors, and everyday difficulties more quickly [44]. For example, ego-resilient individuals tend to use problem-solving abilities and be more persistent in seeking to achieve their goals [45,46]. Previous studies have shown that self-concept and ego-resiliency are associated with academic achievement [1416,47,48]. A meta-analysis found a significant positive association (albeit small in magnitude) between self-concept and academic achievement, even after controlling for the initial level of achievement [15]. The effect of self-concept is also significant after controlling for children’s cognitive abilities [47]. In a similar vein, ego-resiliency has been found positively associated with academic performance in childhood and early adolescence [16,46], even taking cognitive and socioeconomic factors into account [49,50]. Overall, these results provide evidence of the role of negative affect and personal assets in students’ academic achievement, but there is still a paucity of research on how these personal assets take effect in specific academic domains related to mathematics and reading literacy. The vast majority of studies considered how negative affect and personal assets contribute to a single measure of academic achievement (i.e., school grades) [12,32,33,49,51], or in individuals with learning disabilities [5255], or in terms of mathematical achievement [5659]. Measures of reading literacy have been largely neglected, with only a few exceptions [46,47,60,61]. It is consequently still not clear whether the contributions of negative affect and personal assets are similar in explaining mathematics and reading literacy, or whether these variables could have a different influence on these two academic domains [62].

Working memory, negative affect and academic achievement

Among several cognitive abilities, WM seems to be one of the most important to academic success [17,18]. Working memory is a limited-capacity system that enables information to be temporarily stored and manipulated [63,64]. The most classical theorization of WM is the tripartite model involving a central executive system responsible for controlling two subsidiary systems (i.e., the phonological loop and the visuospatial sketchpad) for verbal and visuospatial information [64,65]. Although this model has generated a broad consensus [64], other research has suggested a modality-independent model, in which WM is seen as a domain-general factor, without distinguishing between verbal and visuospatial components [66]. Research has shown that WM is an important facet of academic performance in reading comprehension [67,68] and mathematics achievement [6971]. While there is a general agreement on this positive association between WM and academic achievement, it is only recently that researchers have started to examine the relationship between these aspects and symptoms of anxiety and/or depression.

Recent evidence indicates that anxiety and depressive symptoms could relate, at least in part, to WM. In the case of anxiety, some researchers found that worrying–i.e., cognitive elements of the experience of anxiety, such as negative expectations of oneself [72]–gives rise to task-irrelevant cognitions that reduce the WM available to complete a task [21,73]. A recent meta-analysis found a moderate negative association between anxiety and WM [35]. Similarly, depressive symptoms are characterized by intrusive ruminative thoughts that can interfere with cognitive processes, again reducing the ability to apply cognitive resources to complex cognitive tasks [23,74]. Although previous evidence seemed to suggest that anxiety and depressive symptoms can relate to poor WM, how these aspects relate to students’ academic achievement has not been thoroughly investigated [35].

The present study

The aim of the present study was to assess the specific contributions of negative affect (i.e., general anxiety and depressive symptoms), WM and personal assets (i.e., self-concept, academic and competence dimensions, and ego-resiliency) to mathematics and reading literacy in middle-school students. We opted to consider this particular age group because early adolescence is an important stage of life when individuals are more likely to face emotional difficulties and a decrease in self-concept [37,75]. Confirmatory factor analyses (CFAs) were run to test the structure of the variables considered. Then, given our focus on clarifying the specific contributions of these factors, we conducted a variance decomposition analysis, examining the unique and shared contribution of negative affect (i.e., general anxiety and depressive symptoms), WM and personal assets (i.e., self-concept, academic and competence scales, and ego-resiliency) to mathematics and reading literacy. As regards negative affect and personal assets, these variables were expected to explain a unique portion of variance in both mathematics and reading literacy, even after accounting for WM [35,46,47,50]. As for WM, this ability was expected to explain a large and consistent, unique variance in both mathematics and reading literacy [6770]. Research has also shown that specific emotional aspects (e.g., mathematics anxiety) relate to mathematical performance [56,58,59], while few studies have been conducted on reading literacy [60,76]. Due to the paucity of studies directly comparing mathematics with reading literacy, we assumed that the overall variance explained by negative affect and personal assets would be consistent for both academic domains, while possible differences might be related to WM (see [47]).

Materials and methods


The study involved 144 schoolchildren in grades 6 and 8. Using case-wise deletion with the Mahalanobis distance, one child was found to be a multivariate outlier (D > 49) and was excluded from the analyses, so the final sample included 143 children (females = 50%, agemonths = 150.18, SD = 13.53) in grades 6 (n = 65, agemonths = 136.75, SD = 6.13) and 8 (n = 78, agemonths = 161.37, SD = 5.21). The children came from middle-class families and were attending schools in an urban area of north-east Italy. All the students tested were fluent in Italian. Children with special educational needs, intellectual disabilities, or neurological or genetic disorders were not considered. The study was approved by the Ethics Committee of the University of Padova, Italy. Parents’ written consent and children’s oral assent were obtained before testing.


Negative affect.

The Revised Children’s Manifest Anxiety Scale: Second Edition (RCMAS-2 [20]) is a self-report questionnaire used to identify general anxiety in children and adolescents. It consists of 40 items requiring a yes or no answer, such that higher scores indicate greater general anxiety. The self-report provides scores on worries (e.g., “I feel nervous when things don’t go as I want”), physiological anxiety (e.g., “I often have stomach-ache”) and social anxiety (e.g., “I am worried that my classmates could make fun of me”). The validated Italian version of the tool was used for the present study. As reported in the manual, the RCMAS-2 shows a good internal consistency for the subscales concerning worries (Cronbach’s α = .86), physiological anxiety (Cronbach’s α = .75), and social anxiety (Cronbach’s α = .80) [20].

The Children’s Depression Inventory (CDI; [77]) is a questionnaire for identifying relevant depressive symptoms in children and adolescents. This self-report consists of 27 items comprising three different statements (e.g., “I am sometimes sad”–“I am often sad”–“I am always sad”). For each item, respondents are asked to mark the sentence that best describes how they have been feeling and thinking during the preceding 2 weeks, choosing one of the three options. Each item is associated with a score based on severity, such that higher scores indicate more severe depressive symptoms. As reported in the manual, the CDI shows a good internal consistency for school-aged children (Cronbach’s α = .87) [77].

The Questionnaire for the Assessment of Psychopathology in Adolescence (Q-PAD; [78]) is a self-report questionnaire for assessing behavioral and emotional problems in children and adolescents. The depression scale was used for the present study; it identifies subclinical manifestations (i.e., not necessarily of clinical relevance) of sadness, boredom and melancholy linked to some degree of depression (e.g., “Recently I have felt sad or melancholy most of the time”). There are 8 items scored on a 4-point Likert scale ranging between 1 (“not describing my situation at all”) and 4 (“absolutely describing my situation”), such that higher scores indicate worse depressive symptoms. The manual reports a good internal consistency (Cronbach’s α = .78) [78].

Personal assets.

The Ego-resiliency Scale (ER [43,44]) is an inventory for detecting resilience as a personality trait linked to general resourcefulness, strength of character, and flexibility of functioning (e.g., “I quickly recover from being startled”). The questionnaire consists of 14 statements scored on a 4-point Likert scale from 1 (“does not apply at all”) to 4 (“applies very strongly”), such that higher scores suggest a greater ego-resiliency. For the present study, an Italian translation of the tool, adapted to make the words comprehensible and suitable for children, was used. The internal consistency of the questionnaire was found adequate in the sample involved in the present study (Cronbach’s α = .69).

Multidimensional Self-Concept Scale (MSC[79]) is a self-report tool for assessing self-concept in children and adolescents. For the present study, the Academic (SC-A) and the Competence (SC-C) subscales were used to assess how participants perceived themselves at school (i.e., “Studying is difficult for me”), and their ability to influence their environment, solve problems or achieve their goals (i.e., “I have faith in myself”), respectively. Each subscale consists of 25 statements scored on a 4-point Likert scale from 1 (“absolutely false”) to 4 (“absolutely true”), such that higher scores indicate a more positive self-perception in the corresponding subscales. As reported in the manual, the tool has a good internal consistency for both the Academic and the Competence subscales (Cronbach’s α = .91 and α = .87 respectively) [79].

Working memory tasks.

Verbal WM. Word span—Backward (WS-B; [80]). In the WS-B, lists of words were presented orally at a rate of one item per second and respondents had to recall the words in reverse order. The test proceeded from the shortest list to the longest (containing from two to eight words). No time limit was set for recalling the words in reverse order. The score was the raw number of words accurately recalled in the correct order (min 0, max 70). When calculated for the sample of children considered in this study, the internal consistency was adequate (Cronbach’s alphas .75).

Verbal dual tasks (DT-V [81]). In the DT-V, lists of words of medium-high frequency were presented orally. Each word list included four words, one or more of which were animal nouns. The word lists were organized into increasingly long sets of lists, and respondents were asked to recall the last word of each list in their order of presentation (i.e., from two to six words in all). For each list, they were also asked to press the space bar whenever they heard an animal noun. For instance, the child might hear two lists of words (and therefore have two words to recall, in their order of presentation), followed by three lists of words (with three words to recall) and so on. The score corresponded to the raw number of words accurately recalled at the end of each set of lists (min 0, max 40). Calculated on our sample of children, the internal consistency was adequate (Cronbach’s α = .69).

Listening span test (LST [82]). In the LST, children listened to sentences arranged into sets comprising from two to five sentences. The first set contained two sentences, and the number of sentences gradually increased in subsequent sets. After hearing each sentence, respondents were asked to judge whether the sentence was true or false. Then, after each set of sentences, they were asked to recall the last word in each sentence, in order of presentation. The score corresponded to the raw number of words accurately recalled (min 0, max 28). Calculated on our sample of children, the internal consistency was good (Cronbach’s α = .83).

Visuospatial WM. Matrices spanBackward (MS-B [80]). In the MS-B, the children had to recall the location of black cells that appeared briefly (for one second) in a series of different positions on the screen. Then they were asked to use the mouse to click on the locations where they had previously seen a black cell, in the order in which they had appeared. The number of cells presented in each series ranged from two to eight. The target appeared and disappeared on a grid visible in the middle of the screen. There was no time limit for recalling the cells and the score was the number of cells accurately recalled in the right order (min 0, max 70). Calculated on our sample of children, the internal consistency was good (Cronbach’s α = .79).

Visuospatial dual tasks (DT-VS [83]). The DT-VS consisted in a number of two-dimensional 4 × 4 grids, in which seven of the sixteen cells (i.e., one row and one column) were colored in gray while the others were white. The task was administered in sets of three grids, in which a black dot appeared in one of the cells, then disappeared. Respondents were asked to press the space bar if the dot appeared in a gray cell, and at the same time to remember the position of the last dot (in the third grid in each set). The sets of grids were arranged into six series, each comprising from two to six dots (stimuli) to be remembered (e.g. two stimuli in the first sets and more in later sets). The score corresponded to the raw number of dot positions in the last grid of each set that were accurately recalled, in order of presentation (min 0, max 40). Calculated on the current sample of children, the internal consistency was good (Cronbach’s α = .82).

Dot matrix task (DOT, derived from [84]). For each trial in this task, children were presented with sets of matrix equations to verify (i.e., additions or subtractions with lines in a grid of dots). After each equation, a dot appeared in a 5 × 5 grid and respondents were asked to remember its position, so they had to verify the matrix equation and simultaneously remember the dot’s location. The sets of matrixes were presented in four series of increasing length so that the location of 2 to 5 dots needed to be remembered (with two dots in the first set). The score corresponded to the number of dot locations correctly recalled (min 0, max 28). Calculated on our sample of children, the internal consistency was good (Cronbach’s α = .74).

Mathematics and reading literacy.

The INVALSI (Italian Institute for the Assessment of the Education System [85]) comprises a set of tests widely used all over Italy to assess academic achievement in mathematics and reading literacy on a national scale. There are appropriate versions of the INVALSI tests for each school grade. As regards mathematics, the INVALSI tests provide scores in four areas: space and figures (MATH-SF) includes geometry-related tasks; numbers (MATH-N) measures number operations; relations and functions (MATH-RF) involves solving equivalences or algebraic expressions; and data and prediction (MATH-DP) requires the calculation of simple statistics, such as the probability of an event, or means. The mathematics test takes 75 minutes to complete. In the sample of the present study it showed a good internal consistency (Cronbach’s α = .84 and .85 for grades 6 and 8). As for reading literacy, the INVALSI generates scores relating to reading comprehension and grammar. For reading comprehension (READ-RC), the children were shown two written texts, and asked to answer several multiple-choice or open-ended questions. For grammar (READ-G), they were asked to answer questions on Italian language spelling, morphology, and lexicon. The reading literacy test takes 75 minutes. It showed good psychometric properties in our sample (Cronbach’s α = .87 and .88, for grades 6 and 8).


Participants were tested in different stages: a) in a group session in their classroom, lasting approximately 1 hour, when the self-report measures were administered; b) in individual sessions lasting approximately 30 minutes in a quiet room away from the classroom, when their WM was assessed; and c) in two group sessions lasting 75 minutes each, to test mathematics and reading literacy. As in previous studies, the tasks included in each section were presented in a pseudo-randomized order [47,76]. During the first session (November-December), the children completed the SC-Academic scale [79], the SC-Competence scale [79], the CDI [77], the ER-89 [43,44], the Q-PAD [78] and the RCMAS-2 [20]. In the second session (February-March), they took the WM tests in the following order: 1) MS-B [80]; 2) DT-V[81]; 3) DOT [84]; 4) LST [82]; 5) WS-B[80]; 6) DT-VS [83]. The WM tasks were programmed with E-prime-2 and presented on a 15-inch touchscreen laptop. The partial credit score method was used for scoring purposes [86]. The INVALSI tests [85] on mathematics and reading literacy were proposed during the last two sessions (in May of the same school year). In each session, the children were allowed to take a few minutes to rest between the tasks as necessary. A previously-published article examined subsets of the same data [87], focusing mainly on the influence of verbal and visuospatial WM on mathematics and reading literacy, but none of the analyses presented in this study have already been reported.

Data analysis

Analyses were performed using R statistical software [88]. The “lavaan” library was used to conduct the confirmatory factor analysis (CFA) [89]. Model fit was assessed using various indexes according to the criteria suggested by Hu and Bentler [90], including: the chi-square (χ2); the comparative fit index (CFI); the non-normed fit index (NNFI); the standardized root mean square residual (SRMR); and the root mean square error of approximation (RMSEA). Since different versions of the INVALSI tests were used for the different school grades, item response theory (IRT) scaling, with the two-parameter model (2PL), was adopted to make the results comparable (for the rationale, see [91]). Raw residuals were calculated for each variable, controlling for age in months. In the first set of analyses, we performed a CFA to explore the latent factor structure of our indicators. Then we performed a series of regression analyses, which were then used as the baseline for the variance partitioning analyses (for a similar procedure, see [92]).


Descriptive statistics

Descriptive statistics and correlations are provided in Table 1.

Table 1. Correlations and descriptive statistics (means and standard deviations) after controlling for age in months.

CFA models

In Model 01, we hypothesized the presence of six latent variables: verbal WM (WM-V), visuospatial WM (WM-VS), general anxiety (ANX), depressive symptoms (DEP), personal assets (PER), mathematics (MATH), and reading literacy (READ). The fit of the model proved adequate: χ2(149) = 213.55, p < .001, RMSEA = .055, SRMR = .059, CFI = .946, NNFI = .931. Notably, the correlation between depressive symptoms and anxiety was positive and very high (r = .90), which might mean that these two factors are barely distinguishable. Factor loadings and inter-factor correlations for the model (Model 01) are shown in Table 2.

Table 2. Factor loadings, inter-factor and residual correlations for the final model.

Variance partitioning

To reduce the complexity of the analyses, we considered the overall role of WM, without distinguishing between its verbal and visuospatial components (see [92]), and the overall role of negative affect without distinguishing between depressive symptoms and anxiety. As concerns WM, its verbal and visuospatial aspects are distinguishable, but closely related [93]. The strong positive correlation (r = .70) between verbal and visuospatial WM components tends to produce multicollinearity problems, and this is particularly troublesome for the analyses that we wished to perform. As mentioned previously, anxiety and depressive symptoms were extremely closely related, so these variables were included in a single step. This decision is supported by previous literature suggesting that these aspects are empirically hardly distinguishable in children [30]. In this set of analyses, we used variance partitioning to examine the unique contribution of negative affect, WM and personal assets, and their combinations of shared variance, to mathematics and reading literacy. Several regression analyses were conducted (for a similar procedure, see [94]). As shown in Fig 1, the overall contributions to mathematics and reading literacy were quite similar, though the portion of explained variance was larger for the former (57%) than for the latter (39%). The personal assets variable explained a conspicuous portion of the unique variance in both mathematics and reading literacy (10% and 5%, respectively). The portion of the unique variance explained by the negative affect variable was somewhat smaller (6% for mathematics and 3% for reading literacy). WM tended to explain a larger portion of the unique variance in both the academic domains considered (34% for mathematics and 21% for reading literacy). Intriguingly, the variance shared by WM, personal assets and negative affect was not particularly high (i.e., 4% in both academic domains).

Fig 1.

Variance partitioning for mathematics (top) and reading (bottom). Values ≤ 0 not shown.


The present study adds to the burgeoning literature on the role of negative affect (i.e., general anxiety and depressive symptoms), personal assets (i.e., self-concept, academic and competence dimensions, and ego-resiliency), and WM on mathematics and reading literacy. We focused here on a sample of middle-school students. Unlike the vast majority of such studies, however, we estimated the unique and shared contributions of these variables to mathematics and reading literacy. In particular, negative affect and personal assets were expected to explain a unique portion of variance in both the academic domains considered, even after accounting for WM [35,46,48,50], while WM was expected to explain a large and consistent unique variance on mathematics and reading literacy [6770]. Research has shown that specific emotional aspects (e.g. mathematics anxiety) relate to mathematical performance [56,58,59], while research on reading has been rather limited, so investigating both domains at the same time seems to be of particular interest [76].

Our results show that all the factors considered make some unique contribution to the academic domains investigated. Personal assets were found to explain a portion of the unique variance on both mathematics and reading literacy, a result that confirms previous research and provides evidence of the positive contribution of personal assets to mathematics and reading literacy, even after negative affect and WM have been taken into account [46,47,50]. Personal assets may provide an indication, for example, of how successfully children are studying and mastering their school work, supporting their achievement in both mathematics and reading literacy [14,31,38]. As for negative affect, this variable also explained a unique portion of the variance on both the academic domains considered. Our results are in line with previous findings of a role for negative affect in academic achievement [12]. More importantly, however, they suggest that negative affect can be related to reading literacy as well as mathematics. In particular, anxiety and depressive symptoms can generate a cognitive interference due to emotional distraction [35,95,96]. Our results also show that the contribution of negative affect cannot be subsumed by WM and personal assets: the unique contribution of negative affect was small, but not negligible. It is worth emphasizing that this is one of the first studies to have considered all these variables at once. As concerns WM, our results indicate that this cognitive factor explained a larger portion of the unique variance than either personal assets or negative affect, in both mathematics and reading literacy [67,68,70,71]. We also found that the overall variance in mathematics and reading literacy explained by negative affect, WM and personal assets together differed somewhat. This seems to be due to WM performance, however, which tends–like other higher cognitive functions–to be more strongly related to mathematics [47]. Thus, while negative affect and personal assets both seem to explain a (slightly different) unique portion of the variance in mathematics and reading literacy, further studies are needed to clarify whether general anxiety and depressive symptoms, or ego-resiliency and self-concept could add different, specific contributions to mathematics or reading literacy.

Although our study provides an important contribution to the literature, there are some limitations to consider in future research. For a start, the tests on academic achievement (i.e., the INVALSI), while very reliable, are used to assess children on the national curriculum in Italy, and are only available for grades 6 and 8 (which is why we focused only on these age groups). In addition, our moderate sample size prevented us from comparing our results across genders and school grades. Future studies should replicate our findings in a larger sample and age range, and examine to what extent negative affect, personal assets and academic performance tend to change across different school grades and in relation to gender. Girls seem to experience more anxiety and depression than boys [24,27,97,98]. Other studies that identified gender-related differences in school performance suggested that girls outperform boys at school throughout primary school and up to grade 8 [99]. The extent to which the relationship between emotional problems and academic performance differs between boys and girls is still unclear, however, and further research is needed [12]. Future studies should also examine the role of both general and specific forms of anxiety (e.g., mathematics anxiety, test anxiety) and their interplay with resilience in particular. As suggested by a recent study, different forms of anxiety may co-occur with high levels of general anxiety or academic anxiety (e.g., mathematics and test anxiety) [61,100]. This goes to show that it is important to examine both domain-general and domain-specific individual variables in order to elucidate their effects on academic performance. Finally, further research with a longitudinal design is needed to analyze the reciprocal influences of negative affect, personal assets, WM and academic achievement over time.

Our findings have some important implications. For a start, school-based intervention programs can be proposed for children with emotional difficulties as part of the formal school curriculum or after-school activities [101103]. Prevention and intervention programs focusing on personal assets, such as self-concept and ego-resiliency, might be particularly useful to help children develop new skills and support them in achieving academic success [49,104,105]. Parents and teachers should help children to: a) build a positive overall and academic self-concept by reducing the link between test results and worthiness as a person; b) develop a positive approach to problem-solving in order to cope with difficulties and worries; and c) be aware that poor performance can be part of the learning process, and personal growth [104,106,107]. For example, social-emotional learning (SEL) programs have been found to foster the development of cognitive, affective, and behavioral competences, relationship skills, and responsible decision-making [108,109]. These competences could facilitate academic performance, as reflected in more positive social behavior, less emotional distress, and better test scores and grades [110,111].

To conclude, schoolchildren’s academic achievement seems to be related to several factors, including negative affect, personal assets and WM. The contribution of WM was found stronger than that of the other predictors, but both personal assets (to a larger extent) and negative affect (to a smaller extent) make a specific and shared contribution to mathematics and reading literacy. This finding points to the importance of considering cognitive and individual factors jointly in order to better understand schoolchildren’s academic success.


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