Abstracts

Introduction

Maternal-fetal attachment is the relationship that a pregnant woman establishes with her unborn child and represents the intensity of engaging in behaviors of affiliation and interaction with the fetus in the intrauterine stage ¹1. Cranley MS. Roots of attachment: the relationship of parents with their unborn. Birth Defects Orig Artic Ser 1981; 17:59-83.^,22. Alhusen JL. A literature update on maternal-fetal attachment. J Obstet Gynecol Neonatal Nurs 2008; 37:315-28.. The quality of the attachment between mother and fetus influences the pregnant woman’s health and self-care practices during pregnancy ³3. Pollock PH, Percy A. Maternal antenatal attachment style and potential fetal abuse. Child Abuse Negl 1999; 23:1345-57.^,44. Alhusen JL, Gross D, Hayat MJ, Woods AB, Sharps PW. The influence of maternal-fetal attachment and health practices on neonatal outcomes in low-income, urban women. Res Nurs Health 2012; 35:112-20.. Maternal-fetal attachment affects the mother-baby relationship in the postpartum ⁵5. Doan H, Zimerman A. Prenatal attachment: a developmental model. International Journal of Prenatal and Perinatal Psychology and Medicine 2008; 20:20-8.^,66. Rossen L, Hutchinson D, Wilson J, Burns L, Olsson CA, Allsop S, et al. Predictors of postnatal mother-infant bonding: the role of antenatal bonding, maternal substance use and mental health. Arch Womens Ment Health 2016; 19:609-22.. Disturbances in maternal-fetal attachment may be a marker of early relationship difficulties between a mother and her child and, possibly, indicate a need for early intervention ⁷7. Siddiqui A, Hägglöf B. Does maternal prenatal attachment predict postnatal mother-infant interaction? Early Hum Dev 2000; 59:13-25.^,88. Ertmann RK, Bang CW, Kriegbaum M, Væver MS, Kragstrup J, Siersma V, et al. What factors are most important for the development of the maternal-fetal relationship? A prospective study among pregnant women in Danish general practice. BMC Psychol 2021; 9:2.. Therefore, valid and reliable measurements instruments to assess this construct are essential for scientific research and clinical assistance.

Currently, a range of tools for measuring mother-fetus attachment is available and the Maternal-Fetal Attachment Scale (MFAS) is one of the most used ⁹9. Van den Bergh B, Simons A. A review of scales to measure the mother-foetus relationship. J Reprod Infant Psychol 2009; 27:114-26.. Mecca Cranley published the MFAS in 1981 to measure mother-fetus attachment during pregnancy ¹1. Cranley MS. Roots of attachment: the relationship of parents with their unborn. Birth Defects Orig Artic Ser 1981; 17:59-83.. The items were constructed based on the tasks and behaviors that women develop during pregnancy, combining literature, clinical experience and the judgements of specialists on the subject, and consultation with a group of pregnant women. The final version of MFAS was composed of 24 items distributed in five factors: (1) differentiation of self from the fetus (items 3, 5, 10 e 13), (2) interaction with the fetus (items 1, 7, 17, 20, 24), (3) attributing characteristics and intentions to the fetus (items 6, 9, 12, 14, 16, 21), (4) self-giving (items 2, 11, 15, 22, 23), and (5) role-taking (items 4, 8, 18, 19). The items were scored on a 5-point scale that represents the frequency (from “most of the time” = 5 to “never” = 1). The score ranges from 24 to 120, and higher scores represent higher levels of prenatal attachment. The reliability of the total scale was 0.85 (Cronbach’s alpha) and the factors ranged from 0.52 to 0.73 (scale 1 = 0.62, scale 2 = 0.68, scale 3 = 0.67, scale 4 = 0.52, scale 5 = 0.73). The assessment of factor validity was based on the theoretical assumption of the construct and the correlation analysis between the items and the scale, and no type of factor analysis was performed ¹⁰10. Cranley MS. Development of a tool for the measurement of maternal attachment during pregnancy. Nurs Res 1981; 30:281-4..

MFAS has been widely used in several countries, and most studies indicate adequate reliability for the total score. Nevertheless, some factors present low or regular reliability in multidimensional factorial models. Moreover, none of these studies has confirmed Cranley’s original factorial model ¹¹11. Doan HM, Cox NL, Zimerman A. The maternal fetal attachment scale: some methodological ponderings. J Prenat Perinat Psychol Health 2003; 18:167-88.^,1212. Busonera A, Cataudella S, Lampis J, Tommasi M, Zavattini GC. Psychometric properties of a 20-item version of the Maternal-Fetal Attachment Scale in a sample of Italian expectant women. Midwifery 2016; 34:79-87.. The Italian and German versions of the MFAS suggested a 3D structure, with adequate reliability values for the total score and the first subscale, and regular and poor values for subscales two and three, respectively ¹²12. Busonera A, Cataudella S, Lampis J, Tommasi M, Zavattini GC. Psychometric properties of a 20-item version of the Maternal-Fetal Attachment Scale in a sample of Italian expectant women. Midwifery 2016; 34:79-87.^,1313. Doster A, Wallwiener S, Müller M, Matthies LM, Plewniok K, Feller S, et al. Reliability and validity of the German version of the Maternal-Fetal Attachment Scale. Arch Gynecol Obstet 2018; 297:1157-67..

Feijó ¹⁴14. Feijó MCC. Validação brasileira da Maternal-Fetal Attachment Scale. Arq Bras Psicol (Rio J 1979) 1999; 51:52-62. adapted the MFAS for Brazil in 1999. The author found a multidimensional factorial model with 18 items distributed in five factors. The internal consistency of the total score was regular (Cronbach’s alpha = 0.63). However, the reliability per factor was inadequate (Cronbach’s alpha ranging from 0.56 to -0.18). Due to the low reliability of the subscales, the author argue that only the total score of this Brazilian version of the MFAS should be used. Notably, even the total score of this version of the MFAS showed regular reliability ¹⁴14. Feijó MCC. Validação brasileira da Maternal-Fetal Attachment Scale. Arq Bras Psicol (Rio J 1979) 1999; 51:52-62.. Despite these limitations, the MFAS is the most used instrument to assess maternal-fetal attachment in Brazil ¹⁵15. Ruschel P, Ávila C, Fassini G, Azevedo L, Bilhão N, Paiani R, et al. O apego materno-fetal e a ansiedade da gestante. Rev SBPH 2013; 16:166-77.^,1616. Perrelli JGA, Zambaldi CF, Cantilino A, Sougey EB. Instrumentos de avaliação do vínculo entre mãe e bebê. Rev Paul Pediatr 2014; 32:257-65..

Since the cross-cultural adaptation study in 1999 (more than 20 years ago), there has been no other research on the psychometric properties of the MFAS in Brazil ¹⁴14. Feijó MCC. Validação brasileira da Maternal-Fetal Attachment Scale. Arq Bras Psicol (Rio J 1979) 1999; 51:52-62.. It is necessary to check the validity of instruments over time ¹⁷17. Mokkink LB, de Vet HCW, Prinsen CAC, Patrick DL, Alonso J, Bouter LM, et al. COSMIN risk of bias checklist for systematic reviews of Patient-Reported Outcome Measures. Qual Life Res 2018; 27:1171-9. and reexamine the properties of the MFAS with more modern and accurate methods of psychometric analysis ¹⁸18. Kline R. Principles and practice of structural equation modeling. 4th Ed. New York: The Guildford Press; 2015. in comparison to those used in the cross-cultural adaptation study by Feijó ¹⁴14. Feijó MCC. Validação brasileira da Maternal-Fetal Attachment Scale. Arq Bras Psicol (Rio J 1979) 1999; 51:52-62.. Moreover, the first psychometric study of the MFAS showed an inadequate value of reliability. Therefore, this study aimed to update the psychometric properties of construct validity and reliability of the Brazilian version of the MFAS.

Method

Study design, participants, and procedures

This is part of a cohort study conducted from February 2016 to November 2019 in two Family Health Strategy (FHS) units in the municipality of Rio de Janeiro, Brazil. These health facilities assist a low-income population who lives in precarious sanitation conditions, and the area has the fifth lowest Human Development Index (HDI) in the city. In total, 513 pregnant women with low obstetric risk, with less than 20 weeks of gestational age, and aged 18 years or older were considered eligible for the baseline sample. Three interviews were conducted, the first up to the 20th week of gestation, the second around the 34th week of gestation, and the third interview in the postpartum period. The interviews were conducted by trained interviewers in the prenatal waiting room and lasted about 20 minutes. The MFAS was applied in the second interview and information about guidance received in prenatal consultations and satisfaction with care; use of alcohol, tobacco, and drugs during pregnancy; violence against women during pregnancy were collected. Furthermore, the screening scales for symptoms of anxiety (Patient Health Questionnaire) and depression (Edinburgh Postnatal Depression Scale - EPDS) were applied in this interview. Due to the loss of 105 women (20.19%) between the first and second interviews, the MFAS were applied to 415 pregnant women.

Instruments

The MFAS was created by Cranley in 1981 to assess the mother-fetal attachment ¹⁰10. Cranley MS. Development of a tool for the measurement of maternal attachment during pregnancy. Nurs Res 1981; 30:281-4.. The version of the MFAS used in this study was validated for Brazil in 1999 by Feijó ¹⁴14. Feijó MCC. Validação brasileira da Maternal-Fetal Attachment Scale. Arq Bras Psicol (Rio J 1979) 1999; 51:52-62.. This instrument has no copyright restrictions and can be used freely.

The EPDS was used to assess symptoms of postpartum depression. This instrument was created by Cox et al. ¹⁹19. Cox JL, Holden JM, Sagovsky R. Detection of postnatal depression. Development of the 10-item Edinburgh Postnatal Depression Scale. Br J Psychiatry 1987; 150:782-6. and validated for the Brazilian population by Santos et al. ²⁰20. Santos MF, Martins FC, Pasqual L. Post-natal depression self-rating scales: Brazilian study. Rev Psiquiatr Clín (São Paulo) 1999; 26:90-5.. The EPDS has ten items with score ranging from 0 to 30, and the higher the score, the greater the presence of symptoms of depression ¹⁹19. Cox JL, Holden JM, Sagovsky R. Detection of postnatal depression. Development of the 10-item Edinburgh Postnatal Depression Scale. Br J Psychiatry 1987; 150:782-6..

The Medical Outcome Study (MOS) instrument assessed social support. It is a questionnaire developed by Sherbourne & Stewart ²¹21. Sherbourne CD, Stewart AL. The MOS social support survey. Soc Sci Med 1991; 32:705-14. and validated for Brazilian pregnant women ²²22. Faerstein E, Lopes CS, Valente K, Solé Plá MA, Ferreira MB. Pré-testes de um questionário multidimensional autopreenchível: a experiência do Estudo Pró-Saúde UERJ. Physis (Rio J.) 1999; 9:117-30.. This instrument has 19 items, comprising five functional dimensions of social support: material (four questions - provision of practical resources and material help); affective (three questions - physical displays of love and affection); emotional (four questions - expressions of positive affection, understanding, and feelings of trust); positive social interaction (four questions - availability of people to have fun or relax); and information (four questions - availability of people to obtain advice or guidance). For each item, the woman should indicate how often she considered each type of support available in case of need: never (= 0), rarely (= 1), sometimes (= 2), almost always (= 3), or always (= 4).

The sociodemographic and obstetric data for mothers (age, skin color, marital status, schooling level, wage labor, pregnancy intention, and satisfaction with pregnancy) and social support were obtained from a structured questionnaire administered in the first interview of the cohort study (before 20 gestational weeks).

Data analysis procedures

Descriptive analyses were performed to describe the sample’s sociodemographic profile. The analysis of the construct validity and reliability of MFAS followed three steps. Firstly, the original and the Brazilian factor structure of MFAS were verified by confirmatory factor analysis (CFA) using robust weighted least squares estimator (weighted least squares mean and variance - WLSMV) for parameter estimation, as recommended for categorical data and oblique rotation. The model fit was evaluated by the comparative fit index (CFI), Tucker-Lewis index (TLI), root mean square error of approximation (RMSEA). The values of CFI and TLI > 0.95, and RMSEA < 0.06 were considered well-fitting models. Furthermore, the 90% confidence interval (90%CI) for the RMSEA was calculated and a lower limit close to 0 and an upper limit lower than 0.08 were considered appropriate ²³23. Wang J, Wang X. Structural equation modeling: applications using Mplus. London: Wiley; 2012..

Secondly, to evaluate the factor structure of MFAS, exploratory structural equation models (ESEM) were performed ²⁴24. Marsh HW, Muthén B, Asparouhov T, Lüdtke O, Robitzsch A, Morin AJS, et al. Exploratory structural equation modeling, integrating CFA and EFA: application to students' evaluations of university teaching. Struct Equ Modeling 2009; 16:439-76.. The decision of retaining the number of factors was made by parallel analysis with a random permutation of the observed data ²⁵25. Timmerman ME, Lorenzo-Seva U. Dimensionality assessment of ordered polytomous items with parallel analysis. Psychol Methods 2011; 16:209-20.. The estimator, the type of rotation, and the adjustment indices used were the same as the CFA. Analyses of ESEM started with all instrument items and in each round of analysis, the items loaded in each factor were analyzed. The item should have a load above 0.30 and could not have a cross-load to remain in the model. The item that showed a difference between the two largest loads (which must be greater than 0.30) lower than 0.2 was removed ²⁶26. Hair JF, Black WC, Babin BJ, Anderson RE. Multivariate data analysis. Andover: Cengage Learning; 2019..

Finally, the factorial structure obtained by ESEM was tested via CFA. In this stage, the reliability of each factor of MFAS was tested via the composite reliability coefficient (CR). Convergent and discriminant factor validities were also analyzed. CR and average variance extracted (AVE) are two measures of reliability that can estimate the convergent factor validity. Thus, CR and AVE per factor were estimated using the standardized factor loads of the items and their measurement errors to verify convergent factor validity. Values for CR ≥ 0.7 indicate good reliability and values between 0.6 and 0.7 are acceptable. Values for AVE ≥ 0.5 were considered adequate for convergent validity. The factor discriminant validity analysis was performed by comparing the correlation between the factors and the square root of the AVE. To be considered a good discriminant validity, the square root estimates of the AVE should be higher than the correlation between the factors ²⁶26. Hair JF, Black WC, Babin BJ, Anderson RE. Multivariate data analysis. Andover: Cengage Learning; 2019..

To further examine the construct validity of the MFAS, aiming to test the validity based on external variables, additional hypotheses testing ²⁷27. Mokkink LB, Terwee CB, Patrick DL, Alonso J, Stratford PW, Knol DL, et al. The COSMIN study reached international consensus on taxonomy, terminology, and definitions of measurement properties for health-related patient-reported outcomes. J Clin Epidemiol 2010; 63:737-45. analyses between mother-fetal attachment and obstetric variables (intentionality and satisfaction with pregnancy), social support, and symptoms of perinatal depression was performed by generalized linear model (GLM) using the gamma family. Regression coefficients (β), their respective standard deviations, and p-values obtained by these models were used to verify the association between the variables. A p-value ≤ 0.05 associated with β was considered significant.

Data entry and quality control were performed in the EpiData 3.1 program (http://www.epidata.dk/). All statistical analyses were performed using the R version 3.5.1 (http://www.r-project.org) and MPlus version 8 (http://www.r-project.org). The ESEM and CFA analyses were performed in Mplus version 8.

Ethics

This study was conducted in accordance with Resolution n. 196/1996 of the Brazilian National Health Council, which establishes the standards for studies involving human beings, issued by the Research Ethics Committee of the Sergio Arouca National School of Public Health, Oswaldo Cruz Foundation (ENSP/Fiocruz; CAAE 21982613.6.0000.5240). All participants received and signed an informed consent form.

Results

Participants’ mean age was 26.32 years (standard deviation - SD: 5.86), and most women lived with a partner (78.8%), had 9 to 12 years of education (52.5%), self-declared themselves as mixed-race (49.4%), had a wage labor (53.2%), reported that the pregnancy was intentional (46.3%), and felt satisfied when they found out about the pregnancy (61.9%) (Table 1).

CFA of proposed structural models

The original structural model of MFAS showed good value of RMSEA (0.051; 90%CI: 0.045-0.057) and inadequate values of CFI (0.815) and TLI (0.788). The factor structure of the Brazilian version also obtained good values in RMSEA (0.068; 90%CI: 0.060-0.078), except in the CFI (0.788) and TLI (0.740) (Table 2).

EFA

Since the models tested achieved unsatisfactory fit indices, a series of ESEM were conducted. The ESEM started with 4-factor dimensional structure suggested by parallel analysis as the most representative for the data. In each round, items with a factor loading < 0.30 and/or a cross-load with a difference below 0.2 between the two largest loads (which must be above 0.3) were removed. When an item was removed, a new round of ESEM was performed (Table 3). In the first round of ESEM, items 4 and 15 were excluded for showing cross-loading and items 6, 16, 21, and 22 for low factor loadings (< 0.3). In the second round of ESEM, items 2, 3, 13, and 23 were excluded for cross-loading and items 13 and 23 for low factor loadings (< 0.30).

CFA

The 3-factor model obtained from ESEM showed adequate fit indices in CFA analysis (CFI = 0.969, TLI = 0.960 and RMSEA = 0.032; 90%CI: 0.012-0.048). Four items (Q1, Q11, Q12, Q20) comprise factor 1, three items (Q5, Q8, Q18) were included in factor 2, and five items (Q7, Q9, Q17, Q19, Q24) in the factor 3. The factorial loads varied from 0.390 (item 11) to 0.959 (item 18) and the correlations between the three factors was 0.612 (F1-F2), 0.689 (F1-F3), and 0.569 (F2-F3) (Table 4).

Regarding reliability, the CR of the factors 1 and 2 was adequate (0.72 and 0.82) and the factor 3 was regular (0.63). The overall CR for the instrument was 0.81. Factor 2 presented an AVE > 0.50, and the factors 1 and 3 presented AVE < 0.50 (0.40 and 0.26, respectively). AVE square root of factor 2 (0.78) was greater than the correlation between this factor and factor 1 (0.612) and 3 (0.569), indicating good discriminant validity between this factor and the others. AVE square root of factor 1 (0.63) was greater than the correlation between this factor and factor 2 (0.612) indicating good discriminant validity between this factor and was slightly below than the correlation between this factor and factor 3 (0.689), indicating regular discriminant validity between factor 1 and 3. AVE square root of factor 3 (0.51) was slightly below than the correlation between this factor and factor 2 (0.569), indicating regular discriminant validity between this factor and was lower than the correlation between this factor and factor 1 (0.689), indicating bad discriminant validity between factor 3 and 1 (Table 4). To obtain this final factor model of MFAS, none of the model modification indices were used.

Concerning the hypothesis test (construct validity), the scores on the MFAS scale were positively correlated with social support (p-value < 0.001). Moreover, women who live with a partner (p-value = 0.026) have a better bond with the fetus than those who do not live with or do not have a partner. Women who had intended pregnancies (p-value < 0.001) have a better maternal-fetal bond than those who wanted to wait a little longer or did not want to get pregnant. Women who were satisfied with the pregnancy (p-value < 0.001) had a better bond compared to those who were relatively satisfied or dissatisfied with the pregnancy. Regarding maternal mental health, the greater the presence of depressive symptoms (p-value = 0.007), the worse the bond between mother and fetus (Table 5).

Discussion

The 12-item short version of the Brazilian MFAS presented good construct validity and the factorial validity and hypothesis testing proved to be adequate. This study found a multidimensional factor model, with three factors (“empathy and caring”, “role-taking”, and “interaction with the fetus”) containing 12 items. The association of the instrument total scores with other constructs was consistent with the literature. The reliability of the total score of the instrument proved to be adequate, with the first two subscales obtaining satisfactory reliability indices and the third one regular reliability index.

Following other studies, this analysis did not corroborate the original model ¹²12. Busonera A, Cataudella S, Lampis J, Tommasi M, Zavattini GC. Psychometric properties of a 20-item version of the Maternal-Fetal Attachment Scale in a sample of Italian expectant women. Midwifery 2016; 34:79-87.^,1313. Doster A, Wallwiener S, Müller M, Matthies LM, Plewniok K, Feller S, et al. Reliability and validity of the German version of the Maternal-Fetal Attachment Scale. Arch Gynecol Obstet 2018; 297:1157-67.^,2828. Lingeswaran A, Bindu H. Validation of Tamil version of Cranley's 24-item Maternal-Fetal Attachment Scale in Indian pregnant women. J Obstet Gynaecol India 2012; 62:630-4.. Possibly, these studies employed different analysis methods, leading to different outcomes ²⁶26. Hair JF, Black WC, Babin BJ, Anderson RE. Multivariate data analysis. Andover: Cengage Learning; 2019.. Furthermore, the attachment between mother and fetus may be sensitive to cultural differences ¹1. Cranley MS. Roots of attachment: the relationship of parents with their unborn. Birth Defects Orig Artic Ser 1981; 17:59-83. and removing some items may be partly due to cultural differences. Moreover, the instrument may be temporally outdated since the context of motherhood has changed in recent decades, compromising the items and the factorial structure of the instrument. One change regarding the context of motherhood related to pregnancy that can affect the maternal-fetal attachment is the improvement of ultrasound examinations. These imaging exams are more modern, and mothers can “see” their baby more clearly in the belly (e.g., face, body) and find out the sex of the baby earlier. These changes can impact the development and quality of the maternal-fetal attachment ²⁹29. de Jong-Pleij EA, Ribbert LS, Pistorius LR, Tromp E, Mulder EJ, Bilardo CM. Three-dimensional ultrasound and maternal bonding, a third trimester study and a review. Prenat Diagn 2013; 33:81-8.^,3030. Coté JJ, Badura-Brack AS, Walters RW, Dubay NG, Bredehoeft MR. Randomized controlled trial of the effects of 3D-printed models and 3D ultrasonography on maternal-fetal attachment. J Obstet Gynecol Neonatal Nurs 2020; 49:190-9.. Some of these reasons may also explain why this study does not corroborate the Brazilian version ¹⁴14. Feijó MCC. Validação brasileira da Maternal-Fetal Attachment Scale. Arq Bras Psicol (Rio J 1979) 1999; 51:52-62..

Regarding the structural validity of the MFAS proposed in this study, the first factor corresponds to items 1, 11, 12, and 20. According to the theme of the items, this factor was named “empathy and caring”. Items 1 and 20 represent a caring attitude of the mother towards the fetus, and items 11 and 12 indicate the mother’s empathy towards the fetus. Factor 2 was composed of items 5, 8, and 18. The last two items belong to the factor “role-taking” in the original model, which was maintained in this study. These three items correspond to the “anticipation role-taking” factor in the German version ¹³13. Doster A, Wallwiener S, Müller M, Matthies LM, Plewniok K, Feller S, et al. Reliability and validity of the German version of the Maternal-Fetal Attachment Scale. Arch Gynecol Obstet 2018; 297:1157-67.. In the Italian version, these three items also belong to the factor “future parental role-taking” ¹²12. Busonera A, Cataudella S, Lampis J, Tommasi M, Zavattini GC. Psychometric properties of a 20-item version of the Maternal-Fetal Attachment Scale in a sample of Italian expectant women. Midwifery 2016; 34:79-87.. Factor 3 was composed of items 7, 9, 17, 19, and 24. Like most items, except 9 and 19, these belong to the subscale “interaction with the fetus” of the original scale ¹⁰10. Cranley MS. Development of a tool for the measurement of maternal attachment during pregnancy. Nurs Res 1981; 30:281-4. and remained with the same name. Items 9 (“I can almost guess what my baby’s personality will be from the way they move around”) and 19 (“I try to picture what my baby will look like”) can also be associated with behaviors of interaction between mother and fetus.

Furthermore, item 11 (“I do things to try to stay healthy that I would not do if I were not pregnant”) showed the lowest factorial load in the CFA. This may indicate that taking care of health during pregnancy in the perception of women is motivated more by a certain kind of self-love (taking care of herself) than by the attachment to the baby. Although pregnancy is seen as a time when women are more willing to change their habits and adopt the role of the “good mother” ³¹31. Pedersen S. The good, the bad and the 'good enough' mother on the UK parenting forum Mumsnet. Womens Stud Int Forum 2016; 59:32-8., findings reveal that pregnancy is a time when women think about themselves and their own needs, rather than exclusively focusing on those of their unborn child. The adoption of healthier behaviors during pregnancy is strongly influenced by socioeconomic conditions, which may explain the poor performance of item 11 in the study population. However, for a better understanding of behavioral changes, it is necessary to consider the myriad of internal and external factors that may affect women’s motivation ³²32. Rockliffe L, Peters S, Heazell AEP, Smith DM. Factors influencing health behaviour change during pregnancy: a systematic review and meta-synthesis. Health Psychol Rev 2021; 15:613-32..

Regarding reliability, the convergent validity of the third factor presented regular assessment due to the inadequate AVE value. However, the CR was regular and their items obtained a factorial load above 0.45. These two last parameters corroborate the regular convergent validity ²⁶26. Hair JF, Black WC, Babin BJ, Anderson RE. Multivariate data analysis. Andover: Cengage Learning; 2019., which is not adequate/ideal. Consequently, it is discouraged to use this factor separately from the rest of the instrument. Factor 1 also obtained a regular AVE value; however, its CR showed adequate reliability, indicating that this factor may have acceptable convergent validity.

Discriminant validity was more problematic between factors 1 and 3. One of the explanations for this problem is that factor 1 has two items from Cranley’s original dimension of “interaction with the fetus” ¹⁰10. Cranley MS. Development of a tool for the measurement of maternal attachment during pregnancy. Nurs Res 1981; 30:281-4.. Thus, these two factors showed more problematic/regular discriminant validity. Therefore, there is marginal theoretical convergence between these two factors. Factor 2 presented adequate convergent and discriminant validity.

As the literature indicates, MFAS scores are consistently related to other constructs about hypothesis testing. The association between the MFAS scale with social support is reported in studies that show that social support is an essential factor in developing the mother-fetus attachment ²2. Alhusen JL. A literature update on maternal-fetal attachment. J Obstet Gynecol Neonatal Nurs 2008; 37:315-28.^,3333. Yarcheski A, Mahon NE, Yarcheski TJ, Hanks MM, Cannella BL. A meta-analytic study of predictors of maternal-fetal attachment. Int J Nurs Stud 2009; 46:708-15.. Similarly, living with a partner increases the quality of the bond, thus having a partner may represent a higher perception of social support. Therefore, these results reinforce the importance of the social support to childbearing women. The intention of pregnancy and satisfaction with pregnancy were factors associated with higher levels of maternal-fetal attachment. We found a negative association between MFAS scores and symptoms of depression, mothers with depression were associated with lower levels of maternal-fetal attachment ²2. Alhusen JL. A literature update on maternal-fetal attachment. J Obstet Gynecol Neonatal Nurs 2008; 37:315-28.^,3434. Alvarenga P, Dazzani MVM, Alfaya CAS, Lordelo ER, Piccinini CA. Relações entre a saúde mental da gestante e o apego materno-fetal. Estud Psicol (Natal) 2012; 17:477-84..

This study has some limitations that may have influenced the results. The study was conducted in a low-income population, showing little socioeconomic variability, which may have influenced the item variances. The scale was applied in an interview format, face to face, which may increase the bias of social acceptability, thus women answered to the items with less reliability. Moreover, due to the sample size, we could not confirm or execute the CFA of the structural model obtained by the ESEMs with a distinct sample. Future studies confirming the structural model using a distinct sample from the one used in the exploratory phase are necessary.

Despite the limitations, this study showed that the 12-item short version of the Brazilian MFAS instrument seems to be a reliable and valid instrument to measure maternal-fetal attachment in Brazil. In this way, MFAS can be used in clinical care and scientific research, enabling their expansion and the screening of maternal-fetal bonding problems during prenatal consultations. Therefore, monitoring and strengthening the mother’s bond with her baby during the prenatal period effectively reduces bonding problems after birth.

References

Publication Dates

History