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The Psychometric Properties of the Mental Health Continuum-Short Form (MHC-SF) for Ecuadorian Teenagers

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Title: The Psychometric Properties of the Mental Health Continuum-Short Form (MHC-SF) for Ecuadorian Teenagers
Language: English
Authors: Rodrigo Moreta-Herrera (ORCID 0000-0003-0134-5927), Alberto Rodríguez-Lorenzana, Nazuri Santillán, Micaela Jiménez-Borja, Carlos José Jiménez-Mosquera, Xavier Oriol-Granado, Sergio Domínguez-Lara
Source: Psychology in the Schools. 2025 62(8):2554-2564.
Availability: Wiley. Available from: John Wiley & Sons, Inc. 111 River Street, Hoboken, NJ 07030. Tel: 800-835-6770; e-mail: cs-journals@wiley.com; Web site: https://www.wiley.com/en-us
Peer Reviewed: Y
Page Count: 11
Publication Date: 2025
Document Type: Journal Articles
Reports - Research
Descriptors: Psychometrics, Mental Health, Questionnaires, Foreign Countries, Adolescents, Goodness of Fit, Factor Structure, Well Being, Test Reliability, Test Validity
Geographic Terms: Ecuador
DOI: 10.1002/pits.23485
ISSN: 0033-3085
1520-6807
Abstract: The aim of this study is to find evidence of factorial validity, measure equivalence by gender, and internal consistency of the Mental Health Continuum-Short Form (MHC-SF) in a sample of Ecuadorian teenagers. The study uses a psychometric design to explore the validity and reliability of the measure. Participants of the study were 1154 teenagers between 14 and 19 years of age (mean = 15.69 years; sd = 1.06). In total, 67.7% of participants were women and 32.3% were men. Participants came from 21 cities across Ecuador. This study found that the most appropriate fit for the factorial structure of the MHC-SF is a hierarchical factorial structure with three first-order factors and one second-order factor. The questionnaire presented strict measure invariance amongst women and men and showed differences (p < 0.05) for the latent variables related to the emotional well-being factor. Additionally, the study found that the MHC-SF has high internal consistency. The MHC-SF is a valid measure to evaluate the well-being of Ecuadorian teenagers.
Abstractor: As Provided
Entry Date: 2025
Accession Number: EJ1477447
Database: ERIC
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  Value: &lt;anid&gt;AN0186727902;pis01aug.25;2025Jul21.06:39;v2.2.500&lt;/anid&gt; &lt;title id=&quot;AN0186727902-1&quot;&gt;The Psychometric Properties of the Mental Health Continuum‐Short Form (MHC‐SF) for Ecuadorian Teenagers&#160;&lt;/title&gt; &lt;p&gt;The aim of this study is to find evidence of factorial validity, measure equivalence by gender, and internal consistency of the Mental Health Continuum‐Short Form (MHC‐SF) in a sample of Ecuadorian teenagers. The study uses a psychometric design to explore the validity and reliability of the measure. Participants of the study were 1154 teenagers between 14 and 19 years of age (mean = 15.69 years; sd = 1.06). In total, 67.7% of participants were women and 32.3% were men. Participants came from 21 cities across Ecuador. This study found that the most appropriate fit for the factorial structure of the MHC‐SF is a hierarchical factorial structure with three first‐order factors and one second‐order factor. The questionnaire presented strict measure invariance amongst women and men and showed differences (p &amp;lt; 0.05) for the latent variables related to the emotional well‐being factor. Additionally, the study found that the MHC‐SF has high internal consistency. The MHC‐SF is a valid measure to evaluate the well‐being of Ecuadorian teenagers.&lt;/p&gt; &lt;p&gt;Summary: Availability of measures assessing mental health and well‐being in Ecuadorian adolescents is limited.The MCH‐SF has an adequate fit for adolescents based on a hierarchical configuration and is gender‐invariant.The MHC‐SF is a valid and reliable measure for use in Ecuadorian adolescents.&lt;/p&gt; &lt;p&gt;Keywords: factorial validity; mental health; MHC‐SF; reliability; sex; teenagers&lt;/p&gt; &lt;hd id=&quot;AN0186727902-2&quot;&gt;Introduction&lt;/hd&gt; &lt;p&gt;There is a general consensus amongst mental health professionals today that health cannot be defined merely as the absence of illness. Rather, health is understood as that which permits people to fully experience biopsychosocial well‐being (World Health Organization [WHO]&#160;[&lt;reflink idref=&quot;bib60&quot; id=&quot;ref1&quot;&gt;60&lt;/reflink&gt;]). From this perspective, mental health is understood as a state of well‐being that enables people to deal with everyday stress, maintain a productive and functional life, and contribute meaningfully to their communities, amongst others (World Health Organization [WHO]&#160;[&lt;reflink idref=&quot;bib61&quot; id=&quot;ref2&quot;&gt;61&lt;/reflink&gt;]). This perspective offers a more holistic approach to health which includes physical as well as mental well‐being. From this standpoint, well‐being is fundamental to mental health and has become a central aspect of integrated approaches to mental health care (Diener et al.&#160;[&lt;reflink idref=&quot;bib17&quot; id=&quot;ref3&quot;&gt;17&lt;/reflink&gt;]; Tov et al.&#160;[&lt;reflink idref=&quot;bib59&quot; id=&quot;ref4&quot;&gt;59&lt;/reflink&gt;]). While there is still a tendency to approach mental health through an emphasis on pathologies (Lamers et al.&#160;[&lt;reflink idref=&quot;bib37&quot; id=&quot;ref5&quot;&gt;37&lt;/reflink&gt;]; Godoy‐Izquierdo et al.&#160;[&lt;reflink idref=&quot;bib24&quot; id=&quot;ref6&quot;&gt;24&lt;/reflink&gt;]; S&#225;nchez‐V&#233;lez and Moreta‐Herrera&#160;[&lt;reflink idref=&quot;bib57&quot; id=&quot;ref7&quot;&gt;57&lt;/reflink&gt;]), there is a growing number of studies that seek to understand and evaluate mental well‐being. An emphasis on mental well‐being offers the possibility of underscoring those aspects that contribute to good mental health (Diener et al.&#160;[&lt;reflink idref=&quot;bib17&quot; id=&quot;ref8&quot;&gt;17&lt;/reflink&gt;]).&lt;/p&gt; &lt;p&gt;Defining well‐being as a single construct can be challenging due to its highly subjective nature. However, it can generally be understood as the mastery of various domains: physical (health, nutrition, and hygiene), psychological (pleasure, stability, and mental health), and social (rights, services, and coexistence). These domains enable individuals to relate to others as well as to reach levels of positive self‐reference, happiness, satisfaction, and achievement of personal goals and those of the social context (Kiefer&#160;[&lt;reflink idref=&quot;bib36&quot; id=&quot;ref9&quot;&gt;36&lt;/reflink&gt;]; Dodge et al.&#160;[&lt;reflink idref=&quot;bib18&quot; id=&quot;ref10&quot;&gt;18&lt;/reflink&gt;]). Due to this conceptual difficulty, there are two major approaches that focus on different aspects of well‐being. On the one hand, Hedonic well‐being emphasizes subjective experiences of pleasure, life satisfaction, and happiness as central components of well‐being (Diener et al.&#160;[&lt;reflink idref=&quot;bib17&quot; id=&quot;ref11&quot;&gt;17&lt;/reflink&gt;]). On the other hand, a Eudaimonic approach understands well‐being as arising from a sense of purpose, meaning, and self‐realization. Eudaimonic well‐being seeks to measure the extent to which individuals are able to move beyond immediate self‐gratification in order to develop more prosocial goals. As such, Eudaimonic well‐being looks at how socially functional an individual is (Ryan and Deci&#160;[&lt;reflink idref=&quot;bib56&quot; id=&quot;ref12&quot;&gt;56&lt;/reflink&gt;]). Most studies that seek to offer evaluation tools for mental well‐being have used either a Hedonic or a Eudaimonic approach to define the components of mental well‐being (see Diener et al.&#160;[&lt;reflink idref=&quot;bib17&quot; id=&quot;ref13&quot;&gt;17&lt;/reflink&gt;]). For this reason, there is a need for studies that offer valid and reliable mental well‐being evaluation measures able to capture the complexity of the construct (Diener et al.&#160;[&lt;reflink idref=&quot;bib17&quot; id=&quot;ref14&quot;&gt;17&lt;/reflink&gt;]; Piqueras et al.&#160;[&lt;reflink idref=&quot;bib52&quot; id=&quot;ref15&quot;&gt;52&lt;/reflink&gt;]).&lt;/p&gt; &lt;hd id=&quot;AN0186727902-3&quot;&gt;Evaluating Well‐Being and Validating the MHC‐SF in Teenagers&lt;/hd&gt; &lt;p&gt;As with the adult population, studies exploring well‐being in teenagers have proliferated in recent years (Casas et al.&#160;[&lt;reflink idref=&quot;bib11&quot; id=&quot;ref16&quot;&gt;11&lt;/reflink&gt;]; Gonz&#225;lez‐Carrasco et al.&#160;[&lt;reflink idref=&quot;bib27&quot; id=&quot;ref17&quot;&gt;27&lt;/reflink&gt;]). From a mental health standpoint, adolescence is a particularly vulnerable phase of life because it involves fundamental psychological, emotional, and social developments (Blakemore&#160;[&lt;reflink idref=&quot;bib4&quot; id=&quot;ref18&quot;&gt;4&lt;/reflink&gt;]; Castro‐Ochoa and Moreta‐Herrera&#160;[&lt;reflink idref=&quot;bib12&quot; id=&quot;ref19&quot;&gt;12&lt;/reflink&gt;]). Numerous studies from different countries have shown that beginning at 12 years of age, teenagers suffer an incremental decline in general well‐being (Gonz&#225;lez‐Carrasco et al.&#160;[&lt;reflink idref=&quot;bib26&quot; id=&quot;ref20&quot;&gt;26&lt;/reflink&gt;]). This also includes Ecuadorian teenagers in whom indicators of subjective well‐being indicate alterations due to contextual effects (family situations) during this stage and especially after the Covid‐19 pandemic (Coello et al.&#160;[&lt;reflink idref=&quot;bib16&quot; id=&quot;ref21&quot;&gt;16&lt;/reflink&gt;]; Y&#233;pez‐Tito et al.&#160;[&lt;reflink idref=&quot;bib63&quot; id=&quot;ref22&quot;&gt;63&lt;/reflink&gt;]). Moreover, well‐being is one of the most important indicators of teenage psychological adjustment (Casas&#160;[&lt;reflink idref=&quot;bib10&quot; id=&quot;ref23&quot;&gt;10&lt;/reflink&gt;]). For this reason, developing psychometric tools able to capture this construct as robustly as possible in the teenage population is particularly important.&lt;/p&gt; &lt;p&gt;The Mental Health Continuum Short Form (MHC‐SF), developed by Keyes ([&lt;reflink idref=&quot;bib31&quot; id=&quot;ref24&quot;&gt;31&lt;/reflink&gt;]); Keyes et al. ([&lt;reflink idref=&quot;bib34&quot; id=&quot;ref25&quot;&gt;34&lt;/reflink&gt;]), is a psychometric instrument that integrates both Hedonic well‐being and Eudaimonic well‐being to evaluate positive mental health. Indeed, Keyes ([&lt;reflink idref=&quot;bib32&quot; id=&quot;ref26&quot;&gt;32&lt;/reflink&gt;]) developed the scale based on a conceptual model of subjective well‐being that integrates its psychological and social dimensions. Keyes ([&lt;reflink idref=&quot;bib33&quot; id=&quot;ref27&quot;&gt;33&lt;/reflink&gt;]) argues that it is only in assessing these dimensions of well‐being collectively that we can measure the presence or absence of mental health. To evaluate well‐being in teenagers, Keyes ([&lt;reflink idref=&quot;bib33&quot; id=&quot;ref28&quot;&gt;33&lt;/reflink&gt;]) proposes a dual Mental Health Continuum (MHC) model that includes illness (presence or absence) and three diagnostic levels of positive mental health: flourishing, moderate, and languishing. According to this model, flourishing mental health would consist of a combination of high levels of hedonic and eudaimonic well‐being. The MHC‐SF contains 14 items organized in a three‐factor oblique model (emotional well‐being (EWB), social well‐being (SWB), and psychological well‐being (PWB)). The MHC‐SF has been widely used in a variety of countries and contexts (Żemojtel‐Piotrowska et al.&#160;[&lt;reflink idref=&quot;bib65&quot; id=&quot;ref29&quot;&gt;65&lt;/reflink&gt;]), including Ecuador (Pe&#241;a Contreras et al.&#160;[&lt;reflink idref=&quot;bib51&quot; id=&quot;ref30&quot;&gt;51&lt;/reflink&gt;]) although tested in adults and not in others, even in other groups such as adolescents. These studies have repeatedly substantiated the validity and reliability of the MHC‐SF as an instrument to measure positive mental health in an adult population.&lt;/p&gt; &lt;p&gt;The instrument has also been validated in various studies using a teenage population. Amongst these, various studies have established convergence and divergence validity and confirmed a factorial structure similar to that of Keyes&#39; original model (three‐factor oblique model). For example, a couple of studies from Germany established divergence between the MHC‐SF and measures of anxiety and depression (Kennes et al.&#160;[&lt;reflink idref=&quot;bib30&quot; id=&quot;ref31&quot;&gt;30&lt;/reflink&gt;]; Luijten et al.&#160;[&lt;reflink idref=&quot;bib41&quot; id=&quot;ref32&quot;&gt;41&lt;/reflink&gt;]); a study from South Korea established convergence with measures of life‐satisfaction and self‐esteem (Lim&#160;[&lt;reflink idref=&quot;bib40&quot; id=&quot;ref33&quot;&gt;40&lt;/reflink&gt;]); and a study from Iran established convergence with measures of resilience (Khazaei et al.&#160;[&lt;reflink idref=&quot;bib35&quot; id=&quot;ref34&quot;&gt;35&lt;/reflink&gt;]). Additionally, all of these studies established that the MHC‐SF has adequate internal consistency. Indeed, there is a growing number of research showing that the three‐factor oblique model is an adequate fit for the factorial structure of the MHC‐SF. However, there are some studies that found that a bifactorial model with a general factor and three specific factors was a better fit for their specific studies (Piqueras et al.&#160;[&lt;reflink idref=&quot;bib52&quot; id=&quot;ref35&quot;&gt;52&lt;/reflink&gt;]; S&#246;derqvist and Larm&#160;[&lt;reflink idref=&quot;bib58&quot; id=&quot;ref36&quot;&gt;58&lt;/reflink&gt;]). Additionally, a study with Iranian teenagers fitted various models for the MHC‐SF, including a hierarchical factorial structure with three first‐order factors and one general second‐order factor (Yousefi Afrashteh and Janjani&#160;[&lt;reflink idref=&quot;bib64&quot; id=&quot;ref37&quot;&gt;64&lt;/reflink&gt;]). While this study found that the three oblique factor model had the best fit for the MHC‐SF, the hierarchical model also showed an adequate fit. Given that there is still a lack of consensus regarding the factorial structure of the MHC‐SF for teenagers, it remains important to analyze different factorial structures.&lt;/p&gt; &lt;p&gt;Another property to consider is the measurement equivalence (ME) of the test considering certain variables of interest such as sex among teenagers. The study of sex in the well‐being of teenagers is relevant and although it is not the only factor that can affect well‐being, current gender gaps establish that groups such as women may be more vulnerable to suffering or being affected in their living conditions, health, quality of life, and well‐being (Carmel&#160;[&lt;reflink idref=&quot;bib9&quot; id=&quot;ref38&quot;&gt;9&lt;/reflink&gt;]; Chen et al.&#160;[&lt;reflink idref=&quot;bib15&quot; id=&quot;ref39&quot;&gt;15&lt;/reflink&gt;]), which is why it is essential to have properly calibrated instruments.&lt;/p&gt; &lt;p&gt;ME by sex has been tested using the three‐factor oblique model of the MHC‐SF (Luijten et al.&#160;[&lt;reflink idref=&quot;bib41&quot; id=&quot;ref40&quot;&gt;41&lt;/reflink&gt;]; Yousefi Afrashteh and Janjani&#160;[&lt;reflink idref=&quot;bib64&quot; id=&quot;ref41&quot;&gt;64&lt;/reflink&gt;]; Guo et al.&#160;[&lt;reflink idref=&quot;bib28&quot; id=&quot;ref42&quot;&gt;28&lt;/reflink&gt;]) and so in bifactorial models (Piqueras et al.&#160;[&lt;reflink idref=&quot;bib52&quot; id=&quot;ref43&quot;&gt;52&lt;/reflink&gt;]; Reinhardt et al.&#160;[&lt;reflink idref=&quot;bib55&quot; id=&quot;ref44&quot;&gt;55&lt;/reflink&gt;]); and has only been tested in Iranian teenagers under the hierarchical structure of the scale (Khazaei et al.&#160;[&lt;reflink idref=&quot;bib35&quot; id=&quot;ref45&quot;&gt;35&lt;/reflink&gt;]). In all these cases it is concluded that this invariance condition is met. However, this evidence is still insufficient to establish generality criteria for this property. In this way, the verification of the ME is important to establish conclusions and future considerations on multigroup studies about well‐being and positive mental health using the MHC‐SF plus the sex.&lt;/p&gt; &lt;hd id=&quot;AN0186727902-4&quot;&gt;The Present Study&lt;/hd&gt; &lt;p&gt;In the context of Ecuador, it remains essential to validate measures of well‐being and mental health for teenagers. This is especially urgent given that various studies have shown that Ecuadorian teenagers suffer from significant mental health problems (Barahona et al.&#160;[&lt;reflink idref=&quot;bib3&quot; id=&quot;ref46&quot;&gt;3&lt;/reflink&gt;]; Dominguez‐Lara et al.&#160;[&lt;reflink idref=&quot;bib20&quot; id=&quot;ref47&quot;&gt;20&lt;/reflink&gt;]; Moya‐Sol&#237;s and Moreta‐Herrera&#160;[&lt;reflink idref=&quot;bib50&quot; id=&quot;ref48&quot;&gt;50&lt;/reflink&gt;]; Moreta‐Herrera et al.&#160;[&lt;reflink idref=&quot;bib46&quot; id=&quot;ref49&quot;&gt;46&lt;/reflink&gt;]; Zumba‐Tello and Moreta‐Herrera&#160;[&lt;reflink idref=&quot;bib66&quot; id=&quot;ref50&quot;&gt;66&lt;/reflink&gt;]) that impact levels of well‐being and can even limit their healthy development (Coello et al.&#160;[&lt;reflink idref=&quot;bib16&quot; id=&quot;ref51&quot;&gt;16&lt;/reflink&gt;]; Moreta‐Herrera et al.&#160;[&lt;reflink idref=&quot;bib49&quot; id=&quot;ref52&quot;&gt;49&lt;/reflink&gt;]; Y&#233;pez‐Tito et al.&#160;[&lt;reflink idref=&quot;bib63&quot; id=&quot;ref53&quot;&gt;63&lt;/reflink&gt;]). While there are some mental health measures that have been validated for Ecuadorian teenagers, these instruments tend to evaluate negative mental health or general distress (e.g., Larzabal‐Fernandez et al.&#160;[&lt;reflink idref=&quot;bib38&quot; id=&quot;ref54&quot;&gt;38&lt;/reflink&gt;]). Although in the past few years there has been growing interest in developing instruments for evaluating the well‐being of teenagers, most of these instruments only measure one or a few dimensions of well‐being (e.g., social well‐being, psychological well‐being, or subjective well‐being); so, there is a scarcity of measures based on a holistic understanding of well‐being that includes both hedonic and eudaimonic perspectives (Bravo‐Sanzana et al.&#160;[&lt;reflink idref=&quot;bib5&quot; id=&quot;ref55&quot;&gt;5&lt;/reflink&gt;]). As such, validating a measure, such as the MHC‐SF, that focuses on measuring well‐being from a positive mental health standpoint, is particularly important. Moreover, while the MHC‐SF has been tested in numerous countries and contexts, the measure has yet to be validated in Ecuador and in the Latin American region in general. As such, verifying the psychometric properties of the MHC‐SF for the Ecuadorian teenage population is particularly relevant. Finally, it is necessary to verify that the MHC‐SF is not only applicable to this population segment in general, but also classifying it into subgroups for multigroup analysis by sex, given that this factor is relevant to the course of well‐being and it is necessary that the instrument complies with the ME. If this were not the case, and when using appropriately uncalibrated instruments, measurement bias could be included, given that the differences could be associated with different interpretations of the items in the factorial structure of the measure and not with the characteristics of the groups that cause the differences (Asparouhov and Muth&#233;n&#160;[&lt;reflink idref=&quot;bib1&quot; id=&quot;ref56&quot;&gt;1&lt;/reflink&gt;]; Caycho‐Rodr&#237;guez et al.&#160;[&lt;reflink idref=&quot;bib13&quot; id=&quot;ref57&quot;&gt;13&lt;/reflink&gt;]). For these aspects, the objectives of the present study are to: (a) identify the factorial model that best fits the MHC‐SF in a sample of Ecuadorian teenagers; (b) verify the measure equivalence of the MHC‐SF according to sex; (c) estimate the validity based on the relationship (divergence) with other variables (health perception); and (d) evaluate the internal consistency of the MHC‐SF.&lt;/p&gt; &lt;hd id=&quot;AN0186727902-5&quot;&gt;Methods&lt;/hd&gt; &lt;p&gt;&lt;/p&gt; &lt;hd id=&quot;AN0186727902-6&quot;&gt;Design&lt;/hd&gt; &lt;p&gt;The present research is a psychometric and descriptive study (Ato et al.&#160;[&lt;reflink idref=&quot;bib2&quot; id=&quot;ref58&quot;&gt;2&lt;/reflink&gt;]) that explores the factorial structure, measure equivalence according to sex, and internal consistency of the MHC‐SF in a sample of Ecuadorian teenagers.&lt;/p&gt; &lt;hd id=&quot;AN0186727902-7&quot;&gt;Participants&lt;/hd&gt; &lt;p&gt;This study consisted of a school‐based sample of 1154 teenagers between 14 and 19 years of age (mean = 15.69 years; sd = 1.06). The sample was taken from students at five high schools in the city of Latacunga. In total, 82.8% of participants were enrolled in a public school, 3.4% were enrolled in a private school, and 13.9% were enrolled in a public/religious school. Participants came from 21 cities across Ecuador. In total, 67.7% of the sample were women and 32.3% were men. In total, 91.4% of participants identified as mestizo (91.4%), 7.2% identified as indigenous, 1.1% identified as White, and 0.3% identified as Afro‐Ecuadorian. A total of 34% were enrolled in the first year of high school, 34.7% were enrolled in the second year of high school, and 31.3% were enrolled in the third year of high school.&lt;/p&gt; &lt;p&gt;The sample size is based on an estimated population of adolescents between 14 and 19 years old in the city of Latacunga of 15,186 individuals. Based on a confidence level of 95% and a margin of error of 3%, a sample of at least 997 participants was required, although for the present 1154 valid cases were reached. Participants were selected using nonprobabilistic sampling. The following inclusion criteria were applied: (a) participants should be enrolled in first, second, or third year of high school; (b) tutors or representatives of the participants should have signed the informed consent form beforehand; and (c) participation in the study should be voluntary.&lt;/p&gt; &lt;hd id=&quot;AN0186727902-8&quot;&gt;Instruments&lt;/hd&gt; &lt;p&gt; &lt;emph&gt;The Mental Health Continuum Short Form&lt;/emph&gt; (MHC‐SF; Keyes et al.&#160;[&lt;reflink idref=&quot;bib34&quot; id=&quot;ref59&quot;&gt;34&lt;/reflink&gt;]) translated to Spanish and adapted for an Ecuadorian population (Pe&#241;a Contreras et al.&#160;[&lt;reflink idref=&quot;bib51&quot; id=&quot;ref60&quot;&gt;51&lt;/reflink&gt;]). The MHC‐SF is a 14‐item questionnaire that measures three dimensions of well‐being: EWB (three items), PWB (six items), and SWB (five items). The questionnaire uses a 5‐point Likert scale that ranges from &quot;&lt;emph&gt;Strongly disagree&lt;/emph&gt;&quot; (&lt;reflink idref=&quot;bib1&quot; id=&quot;ref61&quot;&gt;1&lt;/reflink&gt;) to &quot;&lt;emph&gt;Strongly agree&lt;/emph&gt;&quot; (&lt;reflink idref=&quot;bib5&quot; id=&quot;ref62&quot;&gt;5&lt;/reflink&gt;). It is designed to measure positive mental health in a three‐level continuum (flourishing, moderate, and languishing), although in the interpretation of the scores, at the moment there are no normative values that allow categorizing results. High scores on the full scale would indicate flourishing, medium scores moderate, and low scores languishing. As mentioned above, the MHC‐SF presents adequate psychometric properties, highlighting acceptable values of internal consistency (&lt;emph&gt;ɑ&lt;/emph&gt;&lt;subs&gt;(MHC‐SF)&lt;/subs&gt; = 0.87) and a validity of slight divergence with measures of anxiety (&lt;emph&gt;r&lt;/emph&gt; = 0.37) and depression (&lt;emph&gt;r&lt;/emph&gt; = 40) in reference studies with Iranian teenagers in Persian (Yousefi Afrashteh and Janjani&#160;[&lt;reflink idref=&quot;bib64&quot; id=&quot;ref63&quot;&gt;64&lt;/reflink&gt;]).&lt;/p&gt; &lt;p&gt; &lt;emph&gt;The General Health Questionnaire‐28&lt;/emph&gt; (GHQ‐28; Goldberg&#160;[&lt;reflink idref=&quot;bib25&quot; id=&quot;ref64&quot;&gt;25&lt;/reflink&gt;]) translated to Spanish by Godoy‐Izquierdo et al. ([&lt;reflink idref=&quot;bib24&quot; id=&quot;ref65&quot;&gt;24&lt;/reflink&gt;]). The GHQ‐28 is a self‐report measure used to screen for psychological disorders. The questionnaire is made up of four subscales measuring: (a) somatic symptoms (Items 1–7); (b) anxiety/insomnia (Items 8–14); social dysfunction (Items 15–21); and severe depression (Items 22–28). The questionnaire adopts a 4‐point Likert scale ranging from &quot;&lt;emph&gt;Better than usual&lt;/emph&gt;&quot; (0) to &quot;&lt;emph&gt;Much worse than usual&lt;/emph&gt;&quot; (&lt;reflink idref=&quot;bib3&quot; id=&quot;ref66&quot;&gt;3&lt;/reflink&gt;). The GHQ‐28 shows an internal consistency of &lt;emph&gt;α&lt;/emph&gt; = 0.97 and has previously been validated using an Ecuadorian sample (Moreta‐Herrera et al.&#160;[&lt;reflink idref=&quot;bib47&quot; id=&quot;ref67&quot;&gt;47&lt;/reflink&gt;]). The present study found it has an internal consistency of &lt;emph&gt;α&lt;/emph&gt; = 0.94.&lt;/p&gt; &lt;hd id=&quot;AN0186727902-9&quot;&gt;Procedure&lt;/hd&gt; &lt;p&gt;This research first required obtaining the necessary permissions to carry out the study at each high school. Once permission was obtained, we explained the study to all potential participants; this included describing the activities, explaining both measures, and outlining the confidentiality and ethical protocols that would guide the research. Tutors or representatives of students who decided to participate were asked to review and sign the consent form. The data collection process, during which participants filled out the MHC‐SF and the GHQ‐28, was carried out online. Filling out both measures took participants about 15 min in total. Once the data collection process was complete, we proceeded to clean up the data and perform the statistical analysis. It should be noted that the project from which this work is derived followed the specific guidelines and guidelines for the development of the research, both those based on the Declaration of Helsinki for research on human beings and the institutional regulations, taking special consideration in the work with adolescents and the coordination with the legal guardians responsible for the participants.&lt;/p&gt; &lt;hd id=&quot;AN0186727902-10&quot;&gt;Data Analysis&lt;/hd&gt; &lt;p&gt;This study first obtained the descriptive statistics for each item using the mean, standard deviation (sd), skewness (&lt;emph&gt;g&lt;/emph&gt;&lt;subs&gt;1&lt;/subs&gt;), and kurtosis (&lt;emph&gt;g&lt;/emph&gt;&lt;subs&gt;2&lt;/subs&gt;). The assumption of univariant normality was tested using &lt;emph&gt;g&lt;/emph&gt;&lt;subs&gt;1&lt;/subs&gt; and &lt;emph&gt;g&lt;/emph&gt;&lt;subs&gt;2&lt;/subs&gt; values (these should be within &#177;1.5) (Ferrando and Anguiano‐Carrasco&#160;[&lt;reflink idref=&quot;bib22&quot; id=&quot;ref68&quot;&gt;22&lt;/reflink&gt;]). Mardia&#39;s test for multivariant normality was also applied (Mardia&#160;[&lt;reflink idref=&quot;bib42&quot; id=&quot;ref69&quot;&gt;42&lt;/reflink&gt;]). Confirmatory factorial analysis (CFA) was used to test the factorial validity of the MHC‐SF. A diagonal weighted least squares was applied to the polychloric correlation matrix given the absence of multivariant normality (Li&#160;[&lt;reflink idref=&quot;bib39&quot; id=&quot;ref70&quot;&gt;39&lt;/reflink&gt;]). The polychloric correlation matrix was used because of the categorical nature of the items. Three possible models for the factorial structure of the MHC‐SF were compared: (a) a unifactorial model; (b) a three oblique factor model; and (c) a hierarchical model with three first‐order factors and one of second‐order factor.&lt;/p&gt; &lt;p&gt;To test the fit of the MHC‐SF the following criteria were used: chi‐square (&lt;emph&gt;χ&lt;/emph&gt;&lt;sups&gt;2&lt;/sups&gt;), adjusted chi‐square (&lt;emph&gt;χ&lt;/emph&gt;&lt;sups&gt;2&lt;/sups&gt;/&lt;emph&gt;df&lt;/emph&gt;), standardized root mean square residual (SRMR), the Comparative Fit Index (CFI), the Tucker–Lewis Index (TLI), and the factor loadings (&lt;emph&gt;λ&lt;/emph&gt;) for each item. The root mean square error of approximation (RMSEA) was also used as an indicator of model fit because it is not based on centrality. We used the following criteria to decide if a model has a good fit: (a) &lt;emph&gt;χ&lt;/emph&gt;&lt;sups&gt;2&lt;/sups&gt; is not significant or &lt;emph&gt;χ&lt;/emph&gt;&lt;sups&gt;2&lt;/sups&gt;/&lt;emph&gt;df&lt;/emph&gt; is &amp;lt; 4 (this is because the &lt;emph&gt;χ&lt;/emph&gt;&lt;sups&gt;2&lt;/sups&gt; test is sensitive to size and it is highly likely to find statistical significance); (b) the CFI and the TLI are &amp;gt; 0.95; (c) the SRMR and the RMSEA are &amp;lt; 0.06 (although the tolerance can even go up to 0.08) (Byrne&#160;[&lt;reflink idref=&quot;bib7&quot; id=&quot;ref71&quot;&gt;7&lt;/reflink&gt;]; Brown&#160;[&lt;reflink idref=&quot;bib6&quot; id=&quot;ref72&quot;&gt;6&lt;/reflink&gt;]; Dominguez‐Lara&#160;[&lt;reflink idref=&quot;bib19&quot; id=&quot;ref73&quot;&gt;19&lt;/reflink&gt;]; Moreta‐Herrera et al.&#160;[&lt;reflink idref=&quot;bib48&quot; id=&quot;ref74&quot;&gt;48&lt;/reflink&gt;]; Yang‐Wallentin et al.&#160;[&lt;reflink idref=&quot;bib62&quot; id=&quot;ref75&quot;&gt;62&lt;/reflink&gt;]). To justify the hierarchical model, in the oblique model the influence of each factor on the items was valued, from this, the factor loadings were analyzed, which are expected to be &amp;gt; 0.40. Subsequently, the average variance extracted (AVE), which is expected to be &amp;gt; 0.37 (Moral de la Rubia&#160;[&lt;reflink idref=&quot;bib45&quot; id=&quot;ref76&quot;&gt;45&lt;/reflink&gt;]) for each factor as an indicator of convergent internal validity. And the correlations between factors as an indicator of discriminant internal validity (&lt;emph&gt;ϕ&lt;/emph&gt;), in this regard, the high correlations between factors (&lt;emph&gt;ϕ&lt;/emph&gt; &amp;gt; 0.70; Byrne et al.&#160;[&lt;reflink idref=&quot;bib8&quot; id=&quot;ref77&quot;&gt;8&lt;/reflink&gt;]) indicate that the dimensions are not distinguished at an empirical level.&lt;/p&gt; &lt;p&gt;A multigroup confirmatory factorial analysis (MG‐CFA) was applied to the MHC‐SF to verify that both men and women have similar item interpretations within the factorial structure (Asparouhov and Muth&#233;n&#160;[&lt;reflink idref=&quot;bib1&quot; id=&quot;ref78&quot;&gt;1&lt;/reflink&gt;]; Larzabal‐Fernandez et al.&#160;[&lt;reflink idref=&quot;bib38&quot; id=&quot;ref79&quot;&gt;38&lt;/reflink&gt;]). The following procedure was used: first, the MG‐CFA was adjusted independently for men and women. The &lt;emph&gt;χ&lt;/emph&gt;&lt;sups&gt;2&lt;/sups&gt; measure of fit was used to determine if there were differences between both groups. The metric invariance of measure for both groups was tested by constraining factor loadings to be equivalent in the two groups. When metric invariance was supported, we tested for scalar invariance by constraining the item intercepts to be equivalent in the two groups. When scalar invariance was supported, we tested for residual invariance which is when the sum of specific variance and error variance is similar across both groups (Putnick and Bornstein&#160;[&lt;reflink idref=&quot;bib53&quot; id=&quot;ref80&quot;&gt;53&lt;/reflink&gt;]). Residual invariance was tested by constraining the item residuals to be equivalent in the two groups and the constraints for scalar invariance were retained.&lt;/p&gt; &lt;p&gt;Measure invariance was present when the changes (Δ) in the adjustment indices (&lt;emph&gt;χ&lt;/emph&gt;&lt;sups&gt;2&lt;/sups&gt;, CFI, RMSEA) satisfied the following requirements: Δ&lt;emph&gt;χ&lt;/emph&gt;&lt;sups&gt;2&lt;/sups&gt; should be nonsignificant (it should be noted that this statistic is highly conservative and could lead to model rejection due to very small model misspecifications), ΔCFI &amp;gt; −0.010, and ΔRMSEA ≤ 0.010 (Chen&#160;[&lt;reflink idref=&quot;bib14&quot; id=&quot;ref81&quot;&gt;14&lt;/reflink&gt;]), or that ΔCFI &amp;gt; −0.002 and ΔRMSEA ≤ 0.007 (Meade et al.&#160;[&lt;reflink idref=&quot;bib44&quot; id=&quot;ref82&quot;&gt;44&lt;/reflink&gt;]). If strong invariance was present, the difference between latent factor means was analyzed. To determine statistical differences the intercepts of the group of men were set to cero while the intercepts were allowed to vary for the group of women (Δ&lt;subs&gt;&lt;emph&gt;K&lt;/emph&gt;&lt;/subs&gt;). Then, a &lt;emph&gt;t&lt;/emph&gt;‐test was used for independent samples and the size effects (Cohen&#39;s &lt;emph&gt;d&lt;/emph&gt;) were computed to determine if the effect was small, medium, or large (Fritz et al.&#160;[&lt;reflink idref=&quot;bib23&quot; id=&quot;ref83&quot;&gt;23&lt;/reflink&gt;]).&lt;/p&gt; &lt;p&gt;Finally, we computed the McDonald&#39;s &lt;emph&gt;ω&lt;/emph&gt; coefficient to analyze the internal consistency of the measure (&lt;emph&gt;ω&lt;/emph&gt;; McDonald&#160;[&lt;reflink idref=&quot;bib43&quot; id=&quot;ref84&quot;&gt;43&lt;/reflink&gt;]) and its 95% confidence interval (95% CI) for each factor and for the general scale. And the Pearson&#39;s correlation coefficient (&lt;emph&gt;r&lt;/emph&gt;) was computed to establish the association between the variables of the MHC‐SF and the GHQ‐28. This was used to determine whether the degree of divergence between the constructs of both questionnaires was similar. The association criteria to estimate the validity correspond to &lt;emph&gt;r&lt;/emph&gt; = 0.20 as an insignificant association; between 0.20 and 0.50 as small; between 0.50 and 0.80 as moderate and &amp;gt; 0.80 as large (Ferguson&#160;[&lt;reflink idref=&quot;bib21&quot; id=&quot;ref85&quot;&gt;21&lt;/reflink&gt;]).&lt;/p&gt; &lt;p&gt;The programming language used in this study for statistical computing was R version 4.2.2 (R Core Team&#160;[&lt;reflink idref=&quot;bib54&quot; id=&quot;ref86&quot;&gt;54&lt;/reflink&gt;]), together with the &lt;emph&gt;foreign&lt;/emph&gt; for the treatment of the database, &lt;emph&gt;lavaan&lt;/emph&gt; for the factor analyses, &lt;emph&gt;MBESS&lt;/emph&gt; for the study of internal consistency, and &lt;emph&gt;MVN&lt;/emph&gt; for the descriptive analyses of the items and univariate and multivariate normality.&lt;/p&gt; &lt;hd id=&quot;AN0186727902-11&quot;&gt;Results&lt;/hd&gt; &lt;p&gt;&lt;/p&gt; &lt;hd id=&quot;AN0186727902-12&quot;&gt;Descriptive Statistics for Each Item&lt;/hd&gt; &lt;p&gt;Table&#160;1 shows the mean, standard deviation, skewness (&lt;emph&gt;g&lt;/emph&gt;&lt;subs&gt;1&lt;/subs&gt;), and kurtosis (&lt;emph&gt;g&lt;/emph&gt;&lt;subs&gt;2&lt;/subs&gt;) for each item of the MHC‐SF. The mean scores display homogeneity; these range between 2.73 (sd = 1.13) for Item 8 and 3.74 (sd = 1.22&lt;emph&gt;)&lt;/emph&gt; for Item 14. The values of &lt;emph&gt;g&lt;/emph&gt;&lt;subs&gt;1&lt;/subs&gt; and &lt;emph&gt;g&lt;/emph&gt;&lt;subs&gt;2&lt;/subs&gt; are within &#177; 1.5 for all items, indicating that the assumption of normality is appropriate for the scores of each item. Mardia&#39;s test for &lt;emph&gt;g&lt;/emph&gt;&lt;subs&gt;1&lt;/subs&gt; (1725.9) and Mardia&#39;s test for &lt;emph&gt;g&lt;/emph&gt;&lt;subs&gt;2&lt;/subs&gt; (42.7) are both significant, indicating that the assumption of multivariant normality is not appropriate. This shows that we should use robust estimators for the CFA models.&lt;/p&gt; &lt;p&gt;1 Table Descriptive statistics for each item.&lt;/p&gt; &lt;p&gt; &lt;ephtml&gt; &amp;lt;table&amp;gt;&amp;lt;thead valign=&quot;bottom&quot;&amp;gt;&amp;lt;tr valign=&quot;bottom&quot;&amp;gt;&amp;lt;th&amp;gt;Items&amp;lt;/th&amp;gt;&amp;lt;th&amp;gt;Mean&amp;lt;/th&amp;gt;&amp;lt;th&amp;gt;sd&amp;lt;/th&amp;gt;&amp;lt;th&amp;gt;&amp;lt;italic&amp;gt;g&amp;lt;/italic&amp;gt;&amp;lt;sub&amp;gt;1&amp;lt;/sub&amp;gt;&amp;lt;/th&amp;gt;&amp;lt;th&amp;gt;&amp;lt;italic&amp;gt;g&amp;lt;/italic&amp;gt;&amp;lt;sub&amp;gt;2&amp;lt;/sub&amp;gt;&amp;lt;/th&amp;gt;&amp;lt;/tr&amp;gt;&amp;lt;/thead&amp;gt;&amp;lt;tbody valign=&quot;top&quot;&amp;gt;&amp;lt;tr&amp;gt;&amp;lt;td&amp;gt;Me he sentido alegre [I have felt happy]&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;3.34&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;1.10&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;0.05&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;&amp;amp;#8722;1.16&amp;lt;/td&amp;gt;&amp;lt;/tr&amp;gt;&amp;lt;tr&amp;gt;&amp;lt;td&amp;gt;Me he sentido interesado en la vida [I have felt interested in life]&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;3.47&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;1.21&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;&amp;amp;#8722;0.23&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;&amp;amp;#8722;1.08&amp;lt;/td&amp;gt;&amp;lt;/tr&amp;gt;&amp;lt;tr&amp;gt;&amp;lt;td&amp;gt;Me he sentido satisfecho con la vida [I have felt satisfied with life]&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;3.53&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;1.18&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;&amp;amp;#8722;0.21&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;&amp;amp;#8722;1.15&amp;lt;/td&amp;gt;&amp;lt;/tr&amp;gt;&amp;lt;tr&amp;gt;&amp;lt;td&amp;gt;He sentido que tengo algo importante que contribuir a la sociedad [I have felt that I have something important to contribute to society]&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;3.31&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;1.22&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;&amp;amp;#8722;0.04&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;&amp;amp;#8722;1.16&amp;lt;/td&amp;gt;&amp;lt;/tr&amp;gt;&amp;lt;tr&amp;gt;&amp;lt;td&amp;gt;He sentido que pertenezco a una comunidad (a un grupo social como la escuela o el vecindario, etc.) [I have felt that I belong to a community (a social group such as school or neighborhood, etc.)]&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;3.24&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;1.26&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;&amp;amp;#8722;0.06&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;&amp;amp;#8722;1.17&amp;lt;/td&amp;gt;&amp;lt;/tr&amp;gt;&amp;lt;tr&amp;gt;&amp;lt;td&amp;gt;He sentido que nuestra sociedad es un buen lugar para todas las personas [I have felt that our society is a good place for all people]&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;2.99&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;1.25&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;0.29&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;&amp;amp;#8722;1.08&amp;lt;/td&amp;gt;&amp;lt;/tr&amp;gt;&amp;lt;tr&amp;gt;&amp;lt;td&amp;gt;He sentido que las personas son buenas [I have felt that people are good]&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;2.85&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;1.11&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;0.56&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;&amp;amp;#8722;0.75&amp;lt;/td&amp;gt;&amp;lt;/tr&amp;gt;&amp;lt;tr&amp;gt;&amp;lt;td&amp;gt;He sentido que la direcci&amp;amp;#243;n en la que va nuestra sociedad tiene sentido para m&amp;amp;#237; [I have felt that the direction our society is going makes sense to me]&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;2.73&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;1.13&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;0.49&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;&amp;amp;#8722;0.63&amp;lt;/td&amp;gt;&amp;lt;/tr&amp;gt;&amp;lt;tr&amp;gt;&amp;lt;td&amp;gt;He sentido que me gusta la mayor parte de mi personalidad [I have felt that I like most of my personality]&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;3.45&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;1.19&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;&amp;amp;#8722;0.24&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;&amp;amp;#8722;1.03&amp;lt;/td&amp;gt;&amp;lt;/tr&amp;gt;&amp;lt;tr&amp;gt;&amp;lt;td&amp;gt;He sentido que he tenido un buen manejo de mis responsabilidades de la vida diaria [I have felt that I have had a good handle on my daily life responsibilities]&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;3.30&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;1.10&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;0.05&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;&amp;amp;#8722;1.02&amp;lt;/td&amp;gt;&amp;lt;/tr&amp;gt;&amp;lt;tr&amp;gt;&amp;lt;td&amp;gt;He sentido que mis relaciones con los dem&amp;amp;#225;s han sido c&amp;amp;#225;lidas y de confianza [I have felt that my relationships with others have been warm and trusting]&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;3.20&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;1.16&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;0.06&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;&amp;amp;#8722;1.06&amp;lt;/td&amp;gt;&amp;lt;/tr&amp;gt;&amp;lt;tr&amp;gt;&amp;lt;td&amp;gt;Siento que he tenido experiencias que me desafiaron a crecer y convertirme en una mejor persona [I have felt that I have had experiences that challenged me to grow and become a better person]&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;3.49&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;1.11&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;&amp;amp;#8722;0.24&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;&amp;amp;#8722;0.93&amp;lt;/td&amp;gt;&amp;lt;/tr&amp;gt;&amp;lt;tr&amp;gt;&amp;lt;td&amp;gt;Me he sentido seguro al pensar o expresar mis propias ideas y opiniones [I have felt safe thinking or expressing my own ideas and opinions]&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;3.27&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;1.15&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;0.05&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;&amp;amp;#8722;1.10&amp;lt;/td&amp;gt;&amp;lt;/tr&amp;gt;&amp;lt;tr&amp;gt;&amp;lt;td&amp;gt;He sentido que mi vida tiene prop&amp;amp;#243;sito y sentido [I have felt that my life has purpose and meaning]&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;3.74&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;1.22&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;&amp;amp;#8722;0.54&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;&amp;amp;#8722;0.95&amp;lt;/td&amp;gt;&amp;lt;/tr&amp;gt;&amp;lt;tr&amp;gt;&amp;lt;td&amp;gt;Mardia&#39;s test&amp;lt;/td&amp;gt;&amp;lt;td /&amp;gt;&amp;lt;td /&amp;gt;&amp;lt;td&amp;gt;1725.9&amp;lt;ext-link href=&quot;&amp;amp;#42;&quot; /&amp;gt;&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;42.7&amp;lt;ext-link href=&quot;&amp;amp;#42;&quot; /&amp;gt;&amp;lt;/td&amp;gt;&amp;lt;/tr&amp;gt;&amp;lt;/tbody&amp;gt;&amp;lt;/table&amp;gt; &lt;/ephtml&gt; &lt;/p&gt; &lt;p&gt;1 Abbreviations: sd, standard deviation; &lt;emph&gt;g&lt;/emph&gt;&lt;subs&gt;1&lt;/subs&gt;, skewness; &lt;emph&gt;g&lt;/emph&gt;&lt;subs&gt;2&lt;/subs&gt;, kurtosis.&lt;/p&gt; &lt;p&gt;2 * &lt;emph&gt;p&lt;/emph&gt; &amp;lt; 0.001.&lt;/p&gt; &lt;hd id=&quot;AN0186727902-13&quot;&gt;Confirmatory Factorial Analysis (CFA)&lt;/hd&gt; &lt;p&gt;Table&#160;2 shows the fit indices of the unifactorial model, of the three oblique factors model, and of the hierarchical model with three factors of first‐order and one factor of the second‐order. This study omitted the bifactor model because it fit the data poorly. The model used the polychloric correlations matrix of the items. As can be seen in Table&#160;2, the best model was the three oblique factors model; however, the hierarchical model also fits the data well. We concluded that the hierarchical model was preferable because the second‐order factor permits a better interpretation of the items.&lt;/p&gt; &lt;p&gt;2 Table Confirmatory factorial analysis of the MHC‐SF.&lt;/p&gt; &lt;p&gt; &lt;ephtml&gt; &amp;lt;table&amp;gt;&amp;lt;thead valign=&quot;bottom&quot;&amp;gt;&amp;lt;tr valign=&quot;bottom&quot;&amp;gt;&amp;lt;th&amp;gt;Models&amp;lt;/th&amp;gt;&amp;lt;th&amp;gt;&amp;lt;italic&amp;gt;&amp;amp;#967;&amp;lt;/italic&amp;gt;&amp;lt;sup&amp;gt;2&amp;lt;/sup&amp;gt;&amp;lt;/th&amp;gt;&amp;lt;th&amp;gt;&amp;lt;italic&amp;gt;df&amp;lt;/italic&amp;gt;&amp;lt;/th&amp;gt;&amp;lt;th&amp;gt;&amp;lt;italic&amp;gt;&amp;amp;#967;&amp;lt;/italic&amp;gt;&amp;lt;sup&amp;gt;2&amp;lt;/sup&amp;gt;/&amp;lt;italic&amp;gt;df&amp;lt;/italic&amp;gt;&amp;lt;/th&amp;gt;&amp;lt;th&amp;gt;CFI&amp;lt;/th&amp;gt;&amp;lt;th&amp;gt;TLI&amp;lt;/th&amp;gt;&amp;lt;th&amp;gt;SRMR&amp;lt;/th&amp;gt;&amp;lt;th&amp;gt;RMSEA&amp;lt;/th&amp;gt;&amp;lt;/tr&amp;gt;&amp;lt;/thead&amp;gt;&amp;lt;tbody valign=&quot;top&quot;&amp;gt;&amp;lt;tr&amp;gt;&amp;lt;td&amp;gt;Unifactorial&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;721.5&amp;lt;ext-link href=&quot;&amp;amp;#42;&quot; /&amp;gt;&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;77&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;9.4&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;0.989&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;0.987&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;0.054&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;0.085 [0.080&amp;amp;#8211;0.091]&amp;lt;/td&amp;gt;&amp;lt;/tr&amp;gt;&amp;lt;tr&amp;gt;&amp;lt;td&amp;gt;Three oblique factors&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;424.4&amp;lt;ext-link href=&quot;&amp;amp;#42;&quot; /&amp;gt;&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;74&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;5.7&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;0.994&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;0.993&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;0.043&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;0.064 [0.058&amp;amp;#8211;0.071]&amp;lt;/td&amp;gt;&amp;lt;/tr&amp;gt;&amp;lt;tr&amp;gt;&amp;lt;td&amp;gt;Hierarchical&amp;lt;sup&amp;gt;a&amp;lt;/sup&amp;gt;&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;446.3&amp;lt;ext-link href=&quot;&amp;amp;#42;&quot; /&amp;gt;&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;76&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;5.9&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;0.994&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;0.993&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;0.044&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;0.065 [0.059&amp;amp;#8211;0.071]&amp;lt;/td&amp;gt;&amp;lt;/tr&amp;gt;&amp;lt;/tbody&amp;gt;&amp;lt;/table&amp;gt; &lt;/ephtml&gt; &lt;/p&gt; &lt;ulist&gt; &lt;item&gt;3 Abbreviations: &lt;emph&gt;χ&lt;/emph&gt;&lt;sups&gt;2&lt;/sups&gt;, chi‐square; &lt;emph&gt;df&lt;/emph&gt;, degrees of freedom; &lt;emph&gt;χ&lt;/emph&gt;&lt;sups&gt;2&lt;/sups&gt;/&lt;emph&gt;df&lt;/emph&gt;, adjusted chi‐square; CFI, Comparative Fit Index; RMSEA, root mean square error of approximation; SRMR, standardized root mean square residual; TLI, Tucker–Lewis Index.&lt;/item&gt; &lt;item&gt;4 a Three first‐order factors and one second‐order factor.&lt;/item&gt; &lt;item&gt;5 * &lt;emph&gt;p&lt;/emph&gt; &amp;lt; 0.001.&lt;/item&gt; &lt;/ulist&gt; &lt;p&gt;In addition, to estimate the hierarchical model as the most appropriate, previously in the oblique model the factors show limited convergent internal validity with AVE&lt;subs&gt;(EWB)&lt;/subs&gt; = 0.62, AVE&lt;subs&gt;(SWB)&lt;/subs&gt; = 0.35, and AVE&lt;subs&gt;(PWB)&lt;/subs&gt; = 0.31 not fulfilling in all cases the acceptance criterion (AVE &amp;gt; 0.37), while in the discriminant validity, the correlations of the factors &lt;emph&gt;ϕ&lt;/emph&gt;&lt;subs&gt;(EWB–SWB)&lt;/subs&gt; = 0.85; &lt;emph&gt;ϕ&lt;/emph&gt;&lt;subs&gt;(EWB–PWB)&lt;/subs&gt; = 0.87; and &lt;emph&gt;ϕ&lt;/emph&gt;&lt;subs&gt;(SWB–PWB)&lt;/subs&gt; = 0.86 exceed the tolerance (&lt;emph&gt;ϕ&lt;/emph&gt; &amp;gt; 0.70) so their factors are not distinguished at an empirical level. Thus, together with the results of the AFC, the hierarchical model is considered to be the most appropriate (Byrne&#160;[&lt;reflink idref=&quot;bib7&quot; id=&quot;ref87&quot;&gt;7&lt;/reflink&gt;]; Byrne et al.&#160;[&lt;reflink idref=&quot;bib8&quot; id=&quot;ref88&quot;&gt;8&lt;/reflink&gt;]; Brown&#160;[&lt;reflink idref=&quot;bib6&quot; id=&quot;ref89&quot;&gt;6&lt;/reflink&gt;]; Dominguez‐Lara&#160;[&lt;reflink idref=&quot;bib19&quot; id=&quot;ref90&quot;&gt;19&lt;/reflink&gt;]; Moral de la Rubia&#160;[&lt;reflink idref=&quot;bib45&quot; id=&quot;ref91&quot;&gt;45&lt;/reflink&gt;]; Moreta‐Herrera et al.&#160;[&lt;reflink idref=&quot;bib48&quot; id=&quot;ref92&quot;&gt;48&lt;/reflink&gt;]; Yang‐Wallentin et al.&#160;[&lt;reflink idref=&quot;bib62&quot; id=&quot;ref93&quot;&gt;62&lt;/reflink&gt;]).&lt;/p&gt; &lt;p&gt;In this aspect, Figure&#160;1 shows the internal structure of the MHC‐SF for the hierarchical model. The factor loadings (&lt;emph&gt;λ&lt;/emph&gt;) are adequate (&lt;emph&gt;λ&lt;/emph&gt; &amp;gt; 0.40). Hence, the items are relevant to the factorial structure and allow a consistent explanation of the variance. Additionally, the factor loadings (&lt;emph&gt;λ&lt;/emph&gt;) for the second‐order factor are considerably large, which shows that the MHC‐SF has a hierarchical factorial structure.&lt;/p&gt; &lt;p&gt; &lt;img src=&quot;https://imageserver.ebscohost.com/img/embimages/rdk/PIS/01aug25/pits23485-fig-0001.jpg?ephost1=dGJyMNXb4kSepq84yOvqOLCmsE6epq5Srqa4SK6WxWXS&quot; alt=&quot;pits23485-fig-0001.jpg&quot; title=&quot;1 The internal structure of the MHC‐SF for the hierarchical model. EWB, emotional well‐being; MHC‐SF, Mental Health Continuum‐Short Form; PWB, psychological well‐being; SWB, social well‐being.&quot; /&gt; &lt;/p&gt; &lt;p&gt;&lt;/p&gt; &lt;hd id=&quot;AN0186727902-15&quot;&gt;Analysis of the Invariance of the MHC‐SF by Sex&lt;/hd&gt; &lt;p&gt;Table&#160;3 presents the results of applying the MG‐CFA to the MHC‐SF to show the invariance of the measure by sex. First, the CFA was applied for both men and women using each group as a baseline. As can be seen, the adjustment factorial indices are adequate. Also, the difference between the &lt;emph&gt;χ&lt;/emph&gt;&lt;sups&gt;2&lt;/sups&gt; is not significant (Δ&lt;emph&gt;χ&lt;/emph&gt;&lt;sups&gt;2&lt;/sups&gt; = 54.4). As such, it can be concluded that the CFA for both models is similar.&lt;/p&gt; &lt;p&gt;3 Table Analysis of the factorial invariance of the MHC‐SF by sex.&lt;/p&gt; &lt;p&gt; &lt;ephtml&gt; &amp;lt;table&amp;gt;&amp;lt;thead valign=&quot;bottom&quot;&amp;gt;&amp;lt;tr valign=&quot;bottom&quot;&amp;gt;&amp;lt;th&amp;gt;Model&amp;lt;/th&amp;gt;&amp;lt;th&amp;gt;&amp;lt;italic&amp;gt;&amp;amp;#967;&amp;lt;/italic&amp;gt;&amp;lt;sup&amp;gt;2&amp;lt;/sup&amp;gt;&amp;lt;/th&amp;gt;&amp;lt;th&amp;gt;CFI&amp;lt;/th&amp;gt;&amp;lt;th&amp;gt;RMSEA&amp;lt;/th&amp;gt;&amp;lt;th&amp;gt;&amp;amp;#916;&amp;lt;italic&amp;gt;&amp;amp;#967;&amp;lt;/italic&amp;gt;&amp;lt;sup&amp;gt;2&amp;lt;/sup&amp;gt;&amp;lt;/th&amp;gt;&amp;lt;th&amp;gt;&amp;amp;#916;CFI&amp;lt;/th&amp;gt;&amp;lt;th&amp;gt;&amp;amp;#916;RMSEA&amp;lt;/th&amp;gt;&amp;lt;/tr&amp;gt;&amp;lt;/thead&amp;gt;&amp;lt;tbody valign=&quot;top&quot;&amp;gt;&amp;lt;tr&amp;gt;&amp;lt;td&amp;gt;Baseline men&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;(76) 230.5&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;0.991&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;0.074&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;&amp;amp;#8212;&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;&amp;amp;#8212;&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;&amp;amp;#8212;&amp;lt;/td&amp;gt;&amp;lt;/tr&amp;gt;&amp;lt;tr&amp;gt;&amp;lt;td&amp;gt;Baseline women&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;(76) 284.9&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;0.995&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;0.059&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;&amp;amp;#8212;&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;&amp;amp;#8212;&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;&amp;amp;#8212;&amp;lt;/td&amp;gt;&amp;lt;/tr&amp;gt;&amp;lt;tr&amp;gt;&amp;lt;td&amp;gt;Nonrestricted&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;(152) 600.8&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;0.946&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;0.060&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;&amp;amp;#8212;&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;&amp;amp;#8212;&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;&amp;amp;#8212;&amp;lt;/td&amp;gt;&amp;lt;/tr&amp;gt;&amp;lt;tr&amp;gt;&amp;lt;td&amp;gt;Metric&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;(163) 620.3&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;0.943&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;0.059&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;(11) 22.3&amp;lt;ext-link href=&quot;&amp;amp;#42;&quot; /&amp;gt;&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;0.003&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;0.001&amp;lt;/td&amp;gt;&amp;lt;/tr&amp;gt;&amp;lt;tr&amp;gt;&amp;lt;td&amp;gt;Scalar&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;(173) 636.5&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;0.942&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;0.058&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;(10) 14.7&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;0.001&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;0.001&amp;lt;/td&amp;gt;&amp;lt;/tr&amp;gt;&amp;lt;tr&amp;gt;&amp;lt;td&amp;gt;Restricted&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;(177) 646.5&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;0.941&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;0.058&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;(4) 13.2&amp;lt;ext-link href=&quot;&amp;amp;#42;&quot; /&amp;gt;&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;0.001&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;0.000&amp;lt;/td&amp;gt;&amp;lt;/tr&amp;gt;&amp;lt;/tbody&amp;gt;&amp;lt;/table&amp;gt; &lt;/ephtml&gt; &lt;/p&gt; &lt;ulist&gt; &lt;item&gt;6 Abbreviations: &lt;emph&gt;χ&lt;/emph&gt;&lt;sups&gt;2&lt;/sups&gt;, chi‐square; CFI, Comparative Adjustment Index; RMSEA, root mean square error of approximation; Δ, difference.&lt;/item&gt; &lt;item&gt;7 * &lt;emph&gt;p&lt;/emph&gt; &amp;lt; 0.05.&lt;/item&gt; &lt;/ulist&gt; &lt;p&gt;Table&#160;3 then presents the fit indices and the changes of those indices to decide which type of measure invariance is appropriate for the MHC‐SF. The results suggest that the MCH‐SF presents strict measure invariance according to sex.&lt;/p&gt; &lt;p&gt;Given our findings of strong measure invariance and in a complementary way to the instrumental analysis, we proceeded to compare the latent means of both groups for the first‐order factors and the second‐order factor. We found that EWB is the only factor that presents differences between both groups (Δ&lt;subs&gt;&lt;emph&gt;K&lt;/emph&gt;&lt;/subs&gt;&lt;subs&gt;(EWB)&lt;/subs&gt;: intercept of well‐being for women using the restricted model to test strong invariance. Δ&lt;subs&gt;&lt;emph&gt;K&lt;/emph&gt;(EWB)&lt;/subs&gt; = −0.08; &lt;emph&gt;p&lt;/emph&gt; &amp;lt; 0.01). Given that this value is significant, we tested for the difference between the latent means for EWB of men and of women (&lt;emph&gt;t&lt;/emph&gt; = 2.17; &lt;emph&gt;p&lt;/emph&gt; &amp;lt; 0.01). As such, the latent mean for EWB in men is greater than it is in women. Additionally, the effect size (Cohen&#39;s &lt;emph&gt;d&lt;/emph&gt;) is small (Δ&lt;subs&gt;&lt;emph&gt;K&lt;/emph&gt;&lt;/subs&gt;*&lt;subs&gt;(EWB)&lt;/subs&gt; = 0.10.). The rest of the first‐order factors and the second‐order factor for both groups were similar for both groups.&lt;/p&gt; &lt;hd id=&quot;AN0186727902-16&quot;&gt;The Internal Consistency of the MHC‐SF&lt;/hd&gt; &lt;p&gt;Table&#160;4 shows the results of the analyses of the internal consistency of the MHC‐SF. The values of &lt;emph&gt;ω&lt;/emph&gt; ranged between &lt;emph&gt;ω&lt;/emph&gt;&lt;subs&gt;(EWB)&lt;/subs&gt; = 0.80 and &lt;emph&gt;ω&lt;/emph&gt;&lt;subs&gt;(PWB)&lt;/subs&gt; = 0.87 which is acceptable. For the global scale, this range is equivalent to high reliability.&lt;/p&gt; &lt;p&gt;4 Table The internal consistency of the MHC‐SF.&lt;/p&gt; &lt;p&gt; &lt;ephtml&gt; &amp;lt;table&amp;gt;&amp;lt;thead valign=&quot;bottom&quot;&amp;gt;&amp;lt;tr valign=&quot;bottom&quot;&amp;gt;&amp;lt;th&amp;gt;Factors&amp;lt;/th&amp;gt;&amp;lt;th align=&quot;center&quot;&amp;gt;Internal consistency&amp;lt;/th&amp;gt;&amp;lt;/tr&amp;gt;&amp;lt;tr valign=&quot;bottom&quot;&amp;gt;&amp;lt;th&amp;gt;&amp;lt;italic&amp;gt;&amp;amp;#969;&amp;lt;/italic&amp;gt;&amp;lt;/th&amp;gt;&amp;lt;th&amp;gt;95% CI&amp;lt;/th&amp;gt;&amp;lt;/tr&amp;gt;&amp;lt;/thead&amp;gt;&amp;lt;tbody valign=&quot;top&quot;&amp;gt;&amp;lt;tr&amp;gt;&amp;lt;td&amp;gt;Emotional well&amp;amp;#8208;being&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;0.80&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;[0.77&amp;amp;#8211;0.82]&amp;lt;/td&amp;gt;&amp;lt;/tr&amp;gt;&amp;lt;tr&amp;gt;&amp;lt;td&amp;gt;Social well&amp;amp;#8208;being&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;0.81&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;[0.80&amp;amp;#8211;0.83]&amp;lt;/td&amp;gt;&amp;lt;/tr&amp;gt;&amp;lt;tr&amp;gt;&amp;lt;td&amp;gt;Psychological well&amp;amp;#8208;being&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;0.87&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;[0.86&amp;amp;#8211;0.89]&amp;lt;/td&amp;gt;&amp;lt;/tr&amp;gt;&amp;lt;tr&amp;gt;&amp;lt;td&amp;gt;Mental Health Continuum&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;0.92&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;[0.91&amp;amp;#8211;0.93]&amp;lt;/td&amp;gt;&amp;lt;/tr&amp;gt;&amp;lt;/tbody&amp;gt;&amp;lt;/table&amp;gt; &lt;/ephtml&gt; &lt;/p&gt; &lt;p&gt;8 Abbreviations: &lt;emph&gt;ω&lt;/emph&gt;, McDonald&#39;s omega; 95% CI, 95% confidence interval.&lt;/p&gt; &lt;hd id=&quot;AN0186727902-17&quot;&gt;The Divergence of the MHC‐SF With the GHQ‐28&lt;/hd&gt; &lt;p&gt;Table&#160;5 presents the analysis of the divergence of the MHC‐SF with the GHQ‐28 found that the correlations between the factors of each measure and the global GHQ‐28 scale are negative. Hence, the two measures are divergent. The strengths of the relationships between the factors of the two measures were found to be between weak and moderate. Notably, the MHC‐SF relates better with the depression factor of the GHQ‐28 than with the other factors.&lt;/p&gt; &lt;p&gt;5 Table Analysis of the divergence of the MHC‐SF with the GHQ‐28.&lt;/p&gt; &lt;p&gt; &lt;ephtml&gt; &amp;lt;table&amp;gt;&amp;lt;thead valign=&quot;bottom&quot;&amp;gt;&amp;lt;tr valign=&quot;bottom&quot;&amp;gt;&amp;lt;th&amp;gt;Factors&amp;lt;/th&amp;gt;&amp;lt;th align=&quot;center&quot;&amp;gt;Divergence&amp;lt;/th&amp;gt;&amp;lt;/tr&amp;gt;&amp;lt;tr valign=&quot;bottom&quot;&amp;gt;&amp;lt;th&amp;gt;Som&amp;lt;/th&amp;gt;&amp;lt;th&amp;gt;Anx&amp;lt;/th&amp;gt;&amp;lt;th&amp;gt;Dysf&amp;lt;/th&amp;gt;&amp;lt;th&amp;gt;Dep&amp;lt;/th&amp;gt;&amp;lt;th&amp;gt;GHQ&amp;amp;#8208;28&amp;lt;/th&amp;gt;&amp;lt;/tr&amp;gt;&amp;lt;/thead&amp;gt;&amp;lt;tbody valign=&quot;top&quot;&amp;gt;&amp;lt;tr&amp;gt;&amp;lt;td&amp;gt;Emotional well&amp;amp;#8208;being&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;&amp;amp;#8722;0.34&amp;lt;ext-link href=&quot;&amp;amp;#42;&quot; /&amp;gt;&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;&amp;amp;#8722;0.39&amp;lt;ext-link href=&quot;&amp;amp;#42;&quot; /&amp;gt;&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;&amp;amp;#8722;0.38&amp;lt;ext-link href=&quot;&amp;amp;#42;&quot; /&amp;gt;&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;&amp;amp;#8722;0.49&amp;lt;ext-link href=&quot;&amp;amp;#42;&quot; /&amp;gt;&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;&amp;amp;#8722;0.48&amp;lt;ext-link href=&quot;&amp;amp;#42;&quot; /&amp;gt;&amp;lt;/td&amp;gt;&amp;lt;/tr&amp;gt;&amp;lt;tr&amp;gt;&amp;lt;td&amp;gt;Social well&amp;amp;#8208;being&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;&amp;amp;#8722;0.25&amp;lt;ext-link href=&quot;&amp;amp;#42;&quot; /&amp;gt;&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;&amp;amp;#8722;0.27&amp;lt;ext-link href=&quot;&amp;amp;#42;&quot; /&amp;gt;&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;&amp;amp;#8722;0.29&amp;lt;ext-link href=&quot;&amp;amp;#42;&quot; /&amp;gt;&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;&amp;amp;#8722;0.31&amp;lt;ext-link href=&quot;&amp;amp;#42;&quot; /&amp;gt;&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;&amp;amp;#8722;0.33&amp;lt;ext-link href=&quot;&amp;amp;#42;&quot; /&amp;gt;&amp;lt;/td&amp;gt;&amp;lt;/tr&amp;gt;&amp;lt;tr&amp;gt;&amp;lt;td&amp;gt;Psychological well&amp;amp;#8208;being&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;&amp;amp;#8722;0.32&amp;lt;ext-link href=&quot;&amp;amp;#42;&quot; /&amp;gt;&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;&amp;amp;#8722;0.33&amp;lt;ext-link href=&quot;&amp;amp;#42;&quot; /&amp;gt;&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;&amp;amp;#8722;0.38&amp;lt;ext-link href=&quot;&amp;amp;#42;&quot; /&amp;gt;&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;&amp;amp;#8722;0.43&amp;lt;ext-link href=&quot;&amp;amp;#42;&quot; /&amp;gt;&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;&amp;amp;#8722;0.43&amp;lt;ext-link href=&quot;&amp;amp;#42;&quot; /&amp;gt;&amp;lt;/td&amp;gt;&amp;lt;/tr&amp;gt;&amp;lt;tr&amp;gt;&amp;lt;td&amp;gt;Mental Health Continuum&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;&amp;amp;#8722;0.33&amp;lt;ext-link href=&quot;&amp;amp;#42;&quot; /&amp;gt;&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;&amp;amp;#8722;0.36&amp;lt;ext-link href=&quot;&amp;amp;#42;&quot; /&amp;gt;&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;&amp;amp;#8722;0.39&amp;lt;ext-link href=&quot;&amp;amp;#42;&quot; /&amp;gt;&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;&amp;amp;#8722;0.45&amp;lt;ext-link href=&quot;&amp;amp;#42;&quot; /&amp;gt;&amp;lt;/td&amp;gt;&amp;lt;td&amp;gt;&amp;amp;#8722;0.45&amp;lt;ext-link href=&quot;&amp;amp;#42;&quot; /&amp;gt;&amp;lt;/td&amp;gt;&amp;lt;/tr&amp;gt;&amp;lt;/tbody&amp;gt;&amp;lt;/table&amp;gt; &lt;/ephtml&gt; &lt;/p&gt; &lt;ulist&gt; &lt;item&gt;9 Abbreviations: Anx, anxiety/insomnia; Dep, depression; Disf, social dysfunction; Som, somatization.&lt;/item&gt; &lt;item&gt;10 * &lt;emph&gt;p&lt;/emph&gt; &amp;lt; 0.01.&lt;/item&gt; &lt;/ulist&gt; &lt;hd id=&quot;AN0186727902-18&quot;&gt;Discussion&lt;/hd&gt; &lt;p&gt;This study aims to identify the factorial model that best fits the MHC‐SF with a population of Ecuadorian teenagers. The study also seeks to analyze the measure equivalence by sex, the internal consistency of the measure, and the divergence of the MHC‐SF with the GHQ‐28. This study found that both the three‐oblique factor model and the hierarchical second‐order model showed a good fit for the factorial structure of the MHC‐SF. The values of the fit indices are within their accepted tolerance limits (Byrne&#160;[&lt;reflink idref=&quot;bib7&quot; id=&quot;ref94&quot;&gt;7&lt;/reflink&gt;]; Brown&#160;[&lt;reflink idref=&quot;bib6&quot; id=&quot;ref95&quot;&gt;6&lt;/reflink&gt;]; Dominguez‐Lara&#160;[&lt;reflink idref=&quot;bib19&quot; id=&quot;ref96&quot;&gt;19&lt;/reflink&gt;]; Moreta‐Herrera et al.&#160;[&lt;reflink idref=&quot;bib48&quot; id=&quot;ref97&quot;&gt;48&lt;/reflink&gt;]; Yang‐Wallentin et al.&#160;[&lt;reflink idref=&quot;bib62&quot; id=&quot;ref98&quot;&gt;62&lt;/reflink&gt;]). A number of previous studies testing the best fit for the factorial structure of the MHC‐SF with a teenage population had similarly come to the conclusion that the three oblique factor model shows the best fit (Khazaei et al.&#160;[&lt;reflink idref=&quot;bib35&quot; id=&quot;ref99&quot;&gt;35&lt;/reflink&gt;]; Kennes et al.&#160;[&lt;reflink idref=&quot;bib30&quot; id=&quot;ref100&quot;&gt;30&lt;/reflink&gt;]; Lim&#160;[&lt;reflink idref=&quot;bib40&quot; id=&quot;ref101&quot;&gt;40&lt;/reflink&gt;]; Luijten et al.&#160;[&lt;reflink idref=&quot;bib41&quot; id=&quot;ref102&quot;&gt;41&lt;/reflink&gt;]; Yousefi Afrashteh and Janjani&#160;[&lt;reflink idref=&quot;bib64&quot; id=&quot;ref103&quot;&gt;64&lt;/reflink&gt;]). On the other hand, to the best of our knowledge, there has only been a single study testing the fit of a comparable hierarchical factorial structure with a population of Iranian teenagers (Yousefi Afrashteh and Janjani&#160;[&lt;reflink idref=&quot;bib64&quot; id=&quot;ref104&quot;&gt;64&lt;/reflink&gt;]). The findings of that study also found that the three‐oblique factor model showed a better fit, but that the hierarchical structure had an adequate fit as well. On the other hand, the findings of the present study differ from several studies which found that a bifactorial structure was best, when applied with a teenage population (Piqueras et al.&#160;[&lt;reflink idref=&quot;bib52&quot; id=&quot;ref105&quot;&gt;52&lt;/reflink&gt;]; S&#246;derqvist and Larm&#160;[&lt;reflink idref=&quot;bib58&quot; id=&quot;ref106&quot;&gt;58&lt;/reflink&gt;]).&lt;/p&gt; &lt;p&gt;However, this study concludes that while, in line with previous research, the three oblique factor model shows a slightly better fit, the hierarchical model is more appropriate for use with Ecuadorian teenagers because it provides a second‐order global scale that covers the first‐order factors. Additionally, the hierarchical model allows for an interpretation of positive mental health that is better structured, allowing for a superior identification and evaluation of psychological well‐being using a single factor. While Yousefi Afrashteh and Janjani ([&lt;reflink idref=&quot;bib64&quot; id=&quot;ref107&quot;&gt;64&lt;/reflink&gt;]) fitted similar models, to the best of our knowledge, the present study is the first to use the hierarchical model for a better interpretation of the result. As such, further studies are necessary to support and verify our conclusions.&lt;/p&gt; &lt;p&gt;Our findings suggest that the MHC‐SF shows measure invariance according to sex at the strict level. As such, it is understood that the interpretation of the items for both men and women is essentially the same. These findings are similar to previous research with adolescents using the MHC‐SF hierarchical model (Khazaei et al.&#160;[&lt;reflink idref=&quot;bib35&quot; id=&quot;ref108&quot;&gt;35&lt;/reflink&gt;]). Furthermore, it would be estimated from this criterion in future multigroup research based on the sex, that any discrepancies will correspond to particular differences in those groups but not to the factorial structure of the measure (Asparouhov and Muth&#233;n&#160;[&lt;reflink idref=&quot;bib1&quot; id=&quot;ref109&quot;&gt;1&lt;/reflink&gt;]).&lt;/p&gt; &lt;p&gt;Additionally, in the presence of ME at the strong and strict level of the MHC‐SF, the latent means of the groups were compared, and differences were found in that men showed a greater presence of EWB than women. This result at least partially coincides with previous criteria regarding the greater violation of adolescent women&#39;s well‐being (Carmel&#160;[&lt;reflink idref=&quot;bib9&quot; id=&quot;ref110&quot;&gt;9&lt;/reflink&gt;]; Chen et al.&#160;[&lt;reflink idref=&quot;bib15&quot; id=&quot;ref111&quot;&gt;15&lt;/reflink&gt;]). However, these findings must be taken with caution given that they do not correspond to a full multigroup study, but they do establish the importance of verifying the ME of the measure for this type of study.&lt;/p&gt; &lt;p&gt;We confirmed the divergence validity between the MHC‐SF and the GHQ‐28. The depression factor of the GHQ‐28 shows the highest correlation with the MHC‐SF; while the correlations with the other factors (anxiety/insomnia, social dysfunction, and somatization) were lower. In this essence, how psychological symptoms are opposed to processes of mental well‐being and mental health is verified. These findings are consistent with previous research validating the MHC‐SF in teenagers, which found similar tendencies when evaluating emotional distress such as anxiety, depression, stress, among others (Kennes et al.&#160;[&lt;reflink idref=&quot;bib30&quot; id=&quot;ref112&quot;&gt;30&lt;/reflink&gt;]; Luijten et al.&#160;[&lt;reflink idref=&quot;bib41&quot; id=&quot;ref113&quot;&gt;41&lt;/reflink&gt;]; Piqueras et al.&#160;[&lt;reflink idref=&quot;bib52&quot; id=&quot;ref114&quot;&gt;52&lt;/reflink&gt;]; Yousefi Afrashteh and Janjani&#160;[&lt;reflink idref=&quot;bib64&quot; id=&quot;ref115&quot;&gt;64&lt;/reflink&gt;]).&lt;/p&gt; &lt;p&gt;This study found that the internal consistency of the first‐order factors of the MHC‐SF is adequate, while the internal consistency of the second‐order factor of the measure showed high reliability. This indicates that the measure is a reliable instrument to evaluate the well‐being of Ecuadorian teenagers. A number of previous research on the subject also found that the MHC‐SF shows adequate or high levels of internal consistency (Khazaei et al.&#160;[&lt;reflink idref=&quot;bib35&quot; id=&quot;ref116&quot;&gt;35&lt;/reflink&gt;]; Kennes et al.&#160;[&lt;reflink idref=&quot;bib30&quot; id=&quot;ref117&quot;&gt;30&lt;/reflink&gt;]; Lim&#160;[&lt;reflink idref=&quot;bib40&quot; id=&quot;ref118&quot;&gt;40&lt;/reflink&gt;]; Luijten et al.&#160;[&lt;reflink idref=&quot;bib41&quot; id=&quot;ref119&quot;&gt;41&lt;/reflink&gt;]; Yousefi Afrashteh and Janjani&#160;[&lt;reflink idref=&quot;bib64&quot; id=&quot;ref120&quot;&gt;64&lt;/reflink&gt;]).&lt;/p&gt; &lt;p&gt;As such, the findings of this study contribute to a more robust understanding of the internal structure of the MHC‐SF for teenagers and add to the ongoing debate regarding the best way to evaluate psychological well‐being. Indeed, this study offers further support of the validity and reliability of the MHC‐SF and its usefulness in evaluating the well‐being of Ecuadorian teenagers. However, it should be noted that cultural differences may affect the appropriateness of the factorial model that we recommend. In this sense, the MHC‐SF offers an important tool for intervention processes and strategies that guide well‐being and prevent mental health problems, mainly because timely measurement with effective tools allows for more accurate and pertinent diagnoses. In this sense, our findings are particularly relevant given the scarcity of psychometric research on the MHC‐SF in Latin America and Ecuador because it allows for greater availability of validated assessment instruments in adolescents.&lt;/p&gt; &lt;hd id=&quot;AN0186727902-19&quot;&gt;Limitations&lt;/hd&gt; &lt;p&gt;The fundamental limitation of this study is that the sample used in this study was limited to teenagers 14 years of age or older who were enrolled in high school. As such, the findings cannot be extended to teenagers younger than 14 years of age, or to those who are not studying; although the number of teenagers that are not enrolled in high school is low (Instituto Nacional de Estad&#237;sticas y Censos [INEC]&#160;[&lt;reflink idref=&quot;bib29&quot; id=&quot;ref121&quot;&gt;29&lt;/reflink&gt;]). Further research extending the sample of the study to include this cohort is necessary in order to generalize the population group and further confirm the applicability of the proposed factorial model. Another limitation to consider is the absence of normative scores on the scale to categorize the scores into flourishing, moderate, and languishing levels, which is why future studies specialized in this aspect are suggested.&lt;/p&gt; &lt;hd id=&quot;AN0186727902-20&quot;&gt;Conclusion&lt;/hd&gt; &lt;p&gt;This study found that the MHC‐SF is a reliable and valid instrument to evaluate the different dimensions of well‐being in Ecuadorian teenagers. This is particularly important because, in general, there is a scarcity of measures designed to evaluate the well‐being of teenagers. As such, this study contributes to a mounting interest in validating instruments to evaluate the well‐being of teenagers around the world. Since well‐being is a critical indicator of teenage psychological adjustment, developing measures able to capture this construct in the teenage population is particularly important (Casas&#160;[&lt;reflink idref=&quot;bib10&quot; id=&quot;ref122&quot;&gt;10&lt;/reflink&gt;]). In Ecuador in particular, while there are various instruments available to measure psychological distress, this is the first study to test an instrument that measures teenage well‐being from a positive mental health standpoint that understands well‐being as a multidimensional construct. In this sense, the MHC‐SF is particularly interesting because, in measuring the various dimensions of well‐being, it offers a more robust evaluation of the construct. Even these findings not only allow global empirical research into the general validity of the measure, but also for the study of groups specifically classified by sex, given that their ME was confirmed, which will allow us to study the differences in well‐being caused by the existing gaps by groups. In this way, our findings contribute to validating a measure that can be used in the development of interventions (especially to adequately segment and identify the specific needs of individuals) to promote general well‐being in a particularly vulnerable population.&lt;/p&gt; &lt;hd id=&quot;AN0186727902-21&quot;&gt;Acknowledgments&lt;/hd&gt; &lt;p&gt;The authors have nothing to report.&lt;/p&gt; &lt;hd id=&quot;AN0186727902-22&quot;&gt;Ethics Statement&lt;/hd&gt; &lt;p&gt;The research was approved by the Institutional Review Board that corresponds to the Postgraduate Coordination of the Pontificia Universidad Cat&#243;lica del Ecuador Sede Ambato based on the ethical guidelines within the institutional regulations and the Helsinki Convention for research with human beings.&lt;/p&gt; &lt;hd id=&quot;AN0186727902-23&quot;&gt;Consent&lt;/hd&gt; &lt;p&gt;The participants provided written informed consent before participating in this study.&lt;/p&gt; &lt;hd id=&quot;AN0186727902-24&quot;&gt;Conflicts of Interest&lt;/hd&gt; &lt;p&gt;The authors declare no conflicts of interest.&lt;/p&gt; &lt;hd id=&quot;AN0186727902-25&quot;&gt;Data Availability Statement&lt;/hd&gt; &lt;p&gt;The data associated with these results are available to those interested and can be requested from the corresponding author of the study. 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  Label: Title
  Group: Ti
  Data: The Psychometric Properties of the Mental Health Continuum-Short Form (MHC-SF) for Ecuadorian Teenagers
– Name: Language
  Label: Language
  Group: Lang
  Data: English
– Name: Author
  Label: Authors
  Group: Au
  Data: &lt;searchLink fieldCode=&quot;AR&quot; term=&quot;%22Rodrigo+Moreta-Herrera%22&quot;&gt;Rodrigo Moreta-Herrera&lt;/searchLink&gt; (ORCID &lt;externalLink term=&quot;http://orcid.org/0000-0003-0134-5927&quot;&gt;0000-0003-0134-5927&lt;/externalLink&gt;)&lt;br /&gt;&lt;searchLink fieldCode=&quot;AR&quot; term=&quot;%22Alberto+Rodr&#237;guez-Lorenzana%22&quot;&gt;Alberto Rodr&#237;guez-Lorenzana&lt;/searchLink&gt;&lt;br /&gt;&lt;searchLink fieldCode=&quot;AR&quot; term=&quot;%22Nazuri+Santill&#225;n%22&quot;&gt;Nazuri Santill&#225;n&lt;/searchLink&gt;&lt;br /&gt;&lt;searchLink fieldCode=&quot;AR&quot; term=&quot;%22Micaela+Jim&#233;nez-Borja%22&quot;&gt;Micaela Jim&#233;nez-Borja&lt;/searchLink&gt;&lt;br /&gt;&lt;searchLink fieldCode=&quot;AR&quot; term=&quot;%22Carlos+Jos&#233;+Jim&#233;nez-Mosquera%22&quot;&gt;Carlos Jos&#233; Jim&#233;nez-Mosquera&lt;/searchLink&gt;&lt;br /&gt;&lt;searchLink fieldCode=&quot;AR&quot; term=&quot;%22Xavier+Oriol-Granado%22&quot;&gt;Xavier Oriol-Granado&lt;/searchLink&gt;&lt;br /&gt;&lt;searchLink fieldCode=&quot;AR&quot; term=&quot;%22Sergio+Dom&#237;nguez-Lara%22&quot;&gt;Sergio Dom&#237;nguez-Lara&lt;/searchLink&gt;
– Name: TitleSource
  Label: Source
  Group: Src
  Data: &lt;searchLink fieldCode=&quot;SO&quot; term=&quot;%22Psychology+in+the+Schools%22&quot;&gt;&lt;i&gt;Psychology in the Schools&lt;/i&gt;&lt;/searchLink&gt;. 2025 62(8):2554-2564.
– Name: Avail
  Label: Availability
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  Data: Wiley. Available from: John Wiley &amp; Sons, Inc. 111 River Street, Hoboken, NJ 07030. Tel: 800-835-6770; e-mail: cs-journals@wiley.com; Web site: https://www.wiley.com/en-us
– Name: PeerReviewed
  Label: Peer Reviewed
  Group: SrcInfo
  Data: Y
– Name: Pages
  Label: Page Count
  Group: Src
  Data: 11
– Name: DatePubCY
  Label: Publication Date
  Group: Date
  Data: 2025
– Name: TypeDocument
  Label: Document Type
  Group: TypDoc
  Data: Journal Articles&lt;br /&gt;Reports - Research
– Name: Subject
  Label: Descriptors
  Group: Su
  Data: &lt;searchLink fieldCode=&quot;DE&quot; term=&quot;%22Psychometrics%22&quot;&gt;Psychometrics&lt;/searchLink&gt;&lt;br /&gt;&lt;searchLink fieldCode=&quot;DE&quot; term=&quot;%22Mental+Health%22&quot;&gt;Mental Health&lt;/searchLink&gt;&lt;br /&gt;&lt;searchLink fieldCode=&quot;DE&quot; term=&quot;%22Questionnaires%22&quot;&gt;Questionnaires&lt;/searchLink&gt;&lt;br /&gt;&lt;searchLink fieldCode=&quot;DE&quot; term=&quot;%22Foreign+Countries%22&quot;&gt;Foreign Countries&lt;/searchLink&gt;&lt;br /&gt;&lt;searchLink fieldCode=&quot;DE&quot; term=&quot;%22Adolescents%22&quot;&gt;Adolescents&lt;/searchLink&gt;&lt;br /&gt;&lt;searchLink fieldCode=&quot;DE&quot; term=&quot;%22Goodness+of+Fit%22&quot;&gt;Goodness of Fit&lt;/searchLink&gt;&lt;br /&gt;&lt;searchLink fieldCode=&quot;DE&quot; term=&quot;%22Factor+Structure%22&quot;&gt;Factor Structure&lt;/searchLink&gt;&lt;br /&gt;&lt;searchLink fieldCode=&quot;DE&quot; term=&quot;%22Well+Being%22&quot;&gt;Well Being&lt;/searchLink&gt;&lt;br /&gt;&lt;searchLink fieldCode=&quot;DE&quot; term=&quot;%22Test+Reliability%22&quot;&gt;Test Reliability&lt;/searchLink&gt;&lt;br /&gt;&lt;searchLink fieldCode=&quot;DE&quot; term=&quot;%22Test+Validity%22&quot;&gt;Test Validity&lt;/searchLink&gt;
– Name: Subject
  Label: Geographic Terms
  Group: Su
  Data: &lt;searchLink fieldCode=&quot;DE&quot; term=&quot;%22Ecuador%22&quot;&gt;Ecuador&lt;/searchLink&gt;
– Name: DOI
  Label: DOI
  Group: ID
  Data: 10.1002/pits.23485
– Name: ISSN
  Label: ISSN
  Group: ISSN
  Data: 0033-3085&lt;br /&gt;1520-6807
– Name: Abstract
  Label: Abstract
  Group: Ab
  Data: The aim of this study is to find evidence of factorial validity, measure equivalence by gender, and internal consistency of the Mental Health Continuum-Short Form (MHC-SF) in a sample of Ecuadorian teenagers. The study uses a psychometric design to explore the validity and reliability of the measure. Participants of the study were 1154 teenagers between 14 and 19 years of age (mean = 15.69 years; sd = 1.06). In total, 67.7% of participants were women and 32.3% were men. Participants came from 21 cities across Ecuador. This study found that the most appropriate fit for the factorial structure of the MHC-SF is a hierarchical factorial structure with three first-order factors and one second-order factor. The questionnaire presented strict measure invariance amongst women and men and showed differences (p &lt; 0.05) for the latent variables related to the emotional well-being factor. Additionally, the study found that the MHC-SF has high internal consistency. The MHC-SF is a valid measure to evaluate the well-being of Ecuadorian teenagers.
– Name: AbstractInfo
  Label: Abstractor
  Group: Ab
  Data: As Provided
– Name: DateEntry
  Label: Entry Date
  Group: Date
  Data: 2025
– Name: AN
  Label: Accession Number
  Group: ID
  Data: EJ1477447
PLink https://search.ebscohost.com/login.aspx?direct=true&site=eds-live&db=eric&AN=EJ1477447
RecordInfo BibRecord:
  BibEntity:
    Identifiers:
      – Type: doi
        Value: 10.1002/pits.23485
    Languages:
      – Text: English
    PhysicalDescription:
      Pagination:
        PageCount: 11
        StartPage: 2554
    Subjects:
      – SubjectFull: Psychometrics
        Type: general
      – SubjectFull: Mental Health
        Type: general
      – SubjectFull: Questionnaires
        Type: general
      – SubjectFull: Foreign Countries
        Type: general
      – SubjectFull: Adolescents
        Type: general
      – SubjectFull: Goodness of Fit
        Type: general
      – SubjectFull: Factor Structure
        Type: general
      – SubjectFull: Well Being
        Type: general
      – SubjectFull: Test Reliability
        Type: general
      – SubjectFull: Test Validity
        Type: general
      – SubjectFull: Ecuador
        Type: general
    Titles:
      – TitleFull: The Psychometric Properties of the Mental Health Continuum-Short Form (MHC-SF) for Ecuadorian Teenagers
        Type: main
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            NameFull: Rodrigo Moreta-Herrera
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            NameFull: Alberto Rodríguez-Lorenzana
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            NameFull: Nazuri Santillán
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            NameFull: Micaela Jiménez-Borja
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            NameFull: Carlos José Jiménez-Mosquera
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            NameFull: Xavier Oriol-Granado
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            NameFull: Sergio Domínguez-Lara
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          Dates:
            – D: 01
              M: 08
              Type: published
              Y: 2025
          Identifiers:
            – Type: issn-print
              Value: 0033-3085
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              Value: 1520-6807
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          Titles:
            – TitleFull: Psychology in the Schools
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