Clinical indicators of ineffective
airway clearance in children with
acute respiratory infection
Livia Maia Pascoal
1, Marcos Venı´cios de Oliveira Lopes
2,
Viviane Martins da Silva
2, Beatriz Amorim Beltra˜o
2,
Daniel Bruno Resende Chaves
2, T Heather Herdman
3,
Ana Luisa Branda˜o de Carvalho Lira
4,
Iane Ximenes Teixeira
2and Alice Gabrielle de Sousa Costa
2Abstract
The identification of clinical indicators with good predictive ability allows the nurse to minimize the existing variability in clinical situations presented by the patient and to accurately identify the nursing diagnosis, which represents the true clinical condition. The purpose of this study was to analyze the accuracy of NANDA-I clinical indicators of the nursing diagnosis ineffective airway clearance (IAC) in children with acute respiratory infection. This was a prospective cohort study conducted with a group of 136 children and followed for a period of time ranging from 6 to 10 consecutive days. For data analysis, the measures of accuracy were calculated for clinical indicators, which presented statistical significance in a generalized estimated equation model. IAC was present in 91.9% of children in the first assessment. Adventitious breath sounds presented the best measure of accuracy. Ineffective cough presented a high value of sensitivity. Changes in respiratory rate, wide-eyed, diminished breath sounds, and difficulty vocalizing presented high positive pre-dictive values. In conclusion, adventitious breath sounds showed the best prepre-dictive ability to diagnose IAC in children with respiratory acute infection.
Keywords
Clinical validation, diagnostic accuracy, nursing diagnosis, pediatric nursing
1Federal University of Maranha˜o, Fortaleza, Brazil 2Federal University of Ceara´, Fortaleza, Brazil 3NANDA International, Kaukauna, WI, USA
4Federal University of Rio Grande do Norte, Natal, Brazil
Corresponding author:
Marcos Venı´cios de Oliveira Lopes, Federal University of Ceara´, 1055 Esperanto St, Vila Unia˜o. Fortaleza, Ceara´ 60410622, Brazil.
Email: marcos@ufc.br
Journal of Child Health Care 2016, Vol. 20(3) 324–332
Introduction
The establishment of good clinical indicators allows the nurse to minimize the existing variability in the clinical situations presented by the patient and to accurately identify the nursing diagnosis that represents the true clinical condition. Diagnostic accuracy requires a minimum clinical data set for determining the main focus of nursing care, establishing appropriate outcomes and selecting evidence-based interventions. Nurses usually identify a set of defining characteristics and verify a plausible relationship between the diagnostic hypoth-eses based on a specific clinical condition and the characteristics presented by the patient (Lopes et al., 2012).
Defining characteristics with good predictive capability allows the nurse to make assumptions related to the most probable nursing diagnosis for a given situation. This enables clinicians to make the safest inference about the presence of a specific nursing diagnosis. Studies dealing with nursing diagnoses and their components are recommended and encouraged, considering their contribution to honing the skills used by nurses in the diagnostic reasoning process (Lunney, 2009).
In the current clinical validation studies of nursing diagnoses, researchers have used a strategy for assessing the accuracy of the defining characteristics based on the approach used to determine accuracy of diagnostic tests (Beltra˜o et al., 2011; Sousa et al., 2013). In this case, an indicator is treated as a diagnostic test that modifies the estimate of the probability of a diagnosis being present in a given situation. Thus, the accuracy of a clinical indicator is defined as the ability of this indicator to correctly differentiate between individuals with and without a nursing diagnosis (Lopes et al., 2012).
Among the various nursing diagnoses from the NANDA International, Inc1. (NANDA-I) taxonomy, studies highlight those related to the respiratory system. The diagnosis of ineffective airway clearance (IAC) has been investigated, either alone or with other respiratory nursing diagnoses, in several populations, especially hospitalized patients (Monteiro et al., 2006; Silva et al., 2008; Yu¨cel et al., 2011). IAC is defined as the inability to clear secretions or obstructions from the respiratory tract to maintain a clear airway (Herdman and Kamitsuru, 2014: 380). This condition is related to disease processes that contribute to increased secretions and that compro-mise the defense mechanisms of the airways. These processes produce changes that cause retained secretions, excessive mucus, secretions in the bronchi, and exudates in the alveoli (Di Carlo et al., 2010).
Acute respiratory infections (ARIs) stand out among the various clinical conditions associated with IAC. However, it is important to note that the prevalence of clinical indicators and measures of accuracy differ across populations (Cavalcante et al., 2010; Guirao-Goris and Duarte-Climents, 2007; Silveira et al., 2008; Sousa et al., 2013; Zeitoun et al., 2007). For example, a recent sys-tematic review of diagnostic accuracy for clinical indicators of IAC showed that dyspnea had high sensitivity (Se) and specificity (Sp) among children with ARI but had only specificity among adults undergoing cardiac surgery (Sousa et al., 2014).
Methods
One hundred and thirty-six children with ARI were enrolled during hospitalization, and then followed post-discharge, in an open, prospective cohort study for a period of time ranging from 6 to 10 consecutive days, to verify the occurrence of IAC. The study was conducted with patients initially hospitalized in two pediatric hospitals in northeastern Brazil. Ethical approval was obtained from the institutional review board prior to initiation of the study. Parents were informed about the study and signed the terms of free and informed consent prior to data collection.
Children hospitalized for less than 48 hours and aged up to five years were included. In this study, ARI included pneumonia, bronchiolitis, sinusitis, pharyngitis, and tonsillitis diagnosed by physicians from the institution. We chose to work with a wide range of respiratory conditions because many authors recommend that diagnostic accuracy studies include individuals repre-senting the various clinical spectrum of diagnostic interest, increasing the generalizability of the findings (Pepe, 2003; Zhou et al., 2012). Children were excluded if they had chronic diseases that changed the clinical condition of their specific ARI (e.g. congenital heart disease and cerebral palsy).
The sample size was calculated based on 95%confidence level (CI) (Za 2¼
1.96), a conjectured Se value of the clinical indicators equal to 80%(Se¼.8), and a desired width of one-half of the
95%CI of 7%(L¼.07). From these values, the estimated sample size was 126 children based on
the formula presented in Zhou et al. (2012)
n¼½Za
2Seð1SeÞ
L2 :
However, in this study, the final sample consisted of 136 children. Because these children were evaluated for a period of between 6 and 10 consecutive days, the total number of assessments was 1128.
Measurement of variables
Data collection occurred daily over a period of 6 to 10 days, with collection occurring in clinic settings. The children were assessed using a data collection instrument that included the clinical indicators of the IAC nursing diagnosis according to the NANDA-I terminology (Herdman and Kamitsuru, 2014). This instrument was developed from literature on pulmonary evaluation (Jarvis, 2011; Potter and Perry, 2004; Swartz, 2005) and included other clinical information related to the child (gender, medical diagnosis, number of hospitalizations, date of birth, and date of admission). Operational definitions were created for each clinical indicator to be studied, and trained members of a nursing diagnosis research group collected the data. This training lasted eight hours and included a theoretical discussion of diagnostic methods and operational definitions that would be used for data collection. Team members who perform data collection were blinded to the presence/absence of IAC. No discrepancies were found for clinical indicators because the team that collected this information strictly followed these operational definitions. Another team of raters, as described in diagnostic inference section, established the presence/absence of IAC.
Diagnostic inferences
classify individuals with and without this diagnosis, through the analysis of 12 fictitious clinical cases. The aim of this strategy was to enable these nurses to achieve the same level of ability in the diagnostic inference process, as would be evident in their ability to diagnose these cases consistently and uni-formly (Lopes et al., 2012). Ten nurses were divided into pairs for this step in the process, in which they would assess the data to reach a diagnosis for each patient, also known as panel diagnosis.
The use of expert panel diagnosis was described as an important strategy in studies in which no single, error-free test can be used as the gold (reference) standard (Bertens et al., 2013; Rutjes et al., 2007). The purpose of using an expert panel diagnosis as the reference standard is to provide a more accurate and reliable estimate of diagnostic accuracy for clinical indicators. Thus, health-care workers can use these diagnostic accuracy measures to guide their assessments even that does not have the same background of the evaluators in this study.
The 1128 evaluations obtained were divided into five blocks containing approximately 226 clinical cases each. Five different pairs of nurses evaluated the five blocks to determine the presence or absence of IAC. Each pair independently diagnosed the presence or absence of IAC, assessing the same children. The agreement among raters, measured by the coefficient, was
.6861 (z¼17.45,p< .001), which is considered strong. When there was disagreement about the presence of the diagnosis, the criteria for its presence/absence were analyzed by the research team, based upon the assessments.
Statistical analysis
Statistical analysis was performed with the support of the R software, version 3.1.2 (R Core Team, 2014) using the geeM package version 0.7.1 (McDaniel and Henderson, 2014). Unadjusted gen-eralized estimating equation (GEE) models were used to assess the association between each clinical indicator and the presence of IAC.
The GEE model was based on a structure named the autoregressive model of order 1, denoted as AR1, which assumes that the presence of each diagnostic assessment correlates with the presence of this diagnosis in the previous assessment (Van Belle et al., 2004). The indicators that were associated with nursing diagnoses, according to the GEE model, were evaluated based on the measures of accuracy.
The accuracy of clinical indicators was based on the measures of Se, Sp, predictive values (positive and negative), likelihood ratio (positive and negative), and diagnostic odds ratio (OR). The quality of clinical indicators was evaluated from the CIs for the likelihood ratio (positive and negative). In this case, a clinical indicator is considered adequate when the CIs do not contain the value 1.00.
In this research, these measures are defined below, based on the work of Lopes et al. (2012). Sensitivity represents the probability of a clinical indicator being present in patients with the diagnosis in question. Specificity (Sp) represents the probability of the absence of a clinical indicator in patients without the nursing diagnosis. The predictive value, if positive, represents the probability of the nursing diagnosis being present in patients with a specific clinical indicator. If negative, it represents the probability of the absence of the nursing diagnosis in patients without a clinical indicator. The likelihood ratio is the probability of the presence or absence of a clinical indicator in patients with the nursing diagnosis divided by the probability of this indicator in patients without the nursing diagnosis.
Results
most frequent medical diagnosis was pneumonia (85.3%), followed by asthma (18.4%) and pleural
effusion (14.0%). A few children (11.8%) were admitted without the type of respiratory infection
being specified and, in some cases, there was more than one medical diagnosis. The percentage of IAC was 93.9%on the first day and decreases during the follow-up period (90.4%, 94.8%, 81.6%, 77.2%, 72.0%, 51.5%, 41.9%, 30.9%, and 22.8%) showing a statistically significant linear trend (p< .001).
The following clinical indicators of IAC presented frequencies above 60%in the first assess-ment: dyspnea, change in respiratory rate, orthopnea, adventitious breath sounds, and ineffective cough. The indicator, change in respiratory rate, presented the lowest variation in the percentage values throughout the follow-up period. However, ineffective cough presented the highest fre-quency (range: 74.3–95.5%) (Figure 1).
The GEE model showed that the diagnosis of IAC was associated with the following clinical indicators: change in respiratory rate (p¼.007, OR¼2.886), wide-eyed (p< . 001, OR¼68.739), adventitious breath sounds (p< .001, OR¼300.588), decreased breath sounds (p< .001, OR¼ 9.008), ineffective cough (p< .001, OR¼129.530), difficulty vocalizing (p¼.002, OR¼10.042), and cyanosis (p< .001, OR¼.035). These results are presented in Table 1.
However, the CIs for the likelihood ratio for the indicator wide-eyed did not demonstrate improvement in the probability of correctly identifying IAC (Table 2).
Discussion
In this study, the high prevalence of the diagnosis of IAC (91.9%) identified in the first assessment
of children with ARI was similar to that found by Monteiro et al. (2006), in which this diagnosis was manifested by the entire sample. However, other studies (Silva et al., 2008; Silveira et al., 2008; Sousa et al., 2013) have shown a different prevalence of IAC, with values ranging from 31%
to 66.7%. This variability may be related to several factors, such as the pathophysiology of the clinical condition of the patient, the age-group of the study population, and the sample size.
In a similar study (Silveira et al., 2008) conducted on patients with asthma, the clinical indicator adventitious breath sounds presented similar values of Se (96.43), a PVþ(84.38) and PV(90.00), Table 1.Results of the unadjusted GEE model for all assessments using IAC as the response variable (yes or no) and entering individual clinical indicators as explanatory variables in the model using AR1.
Clinical indicators OR 95%CI pValue
Restlessness .967 .371 2.521 .945 Cyanosis .035 .006 .197 <.001 Dyspnea 1.056 .358 3.119 .921 Excessive sputum .802 .322 1.999 .636 Change in respiratory rate 2.886 1.344 6.198 .007 Change in respiratory rhythm 3.222 .859 12.084 .083 Wide-eyed 68.739 1.531 3086.704 <.001 Orthopnea 2.029 .447 9.216 .359 Adventitious breath sounds 300.588 43.673 2068.869 <.001 Diminished breath Sounds 9.008 2.752 29.484 <.001 Absent cougha – – – – Ineffective cough 129.530 33.409 502.197 <.001 Difficulty vocalizing 10.042 2.381 42.355 .002
Note:GEE: generalized estimating equation; IAC: ineffective airway clearance; CI: confidence interval; AR1: autoregressive model of order one.
aNo convergence of the model.
Table 2.Measures of accuracy for the clinical indicators of IAC in children with acute respiratory infection.
Clinical Indicators Se Sp PVþ PV LRþ(95%CI) LR(95%CI) ROC
Cyanosis 0.56 99.16 71.43 20.96 0.66 [0.17–2.65] 1.00 [0.99–1.02] 0.498 Change in respiratory rate 59.48 55.27 83.33 26.63 1.33 [1.14–1.55] 0.73 [0.64–.084] 0.573 Wide-eyed 0.45 99.58 80.00 21.12 1.07 [0.15–7.58] 1.00 [0.99–1.01] 0.500 Adventitious breath sounds 81.48 96.62 98.91 58.12 24.14 [12.21–47.73] 0.19 [0.17–0.22] 0.890 Diminished breath Sounds 37.93 80.59 88.02 25.67 1.95 [1.50–2.55] 0.77 [0.71–0.83] 0.592 Ineffective cough 97.81 59.74 92.84 83.64 2.43 [2.00–2.95] 0.04 [0.02–0.06] 0.787 Difficulty vocalizing 11.00 97.05 93.33 22.48 3.72 [1.79–7.75] 0.92 [0.89–0.95] 0.540
when compared with those found in the present investigation. Furthermore, the observed pro-portion of this clinical indicator was similar to that reported in other surveys of asthmatic children. For example, in the study by Silveira et al. (2008), the proportion was 76.2%. The studies of Chagas et al. (2011) and Mendes et al. (2012) found frequencies of 100%and 92.9%, respectively. However, in patients with cardiovascular heart disease, the adventitious breath sounds presented values below 62.5%(Fontes and Cruz, 2007; Martins and Gutie´rrez, 2005).
Regarding the indicator diminished breath sounds, the children included in this study presented measures of accuracy similar to those found by Silveira et al. (2008), who obtained values of 78.57%for Se and 85.71%for PVþ. In contrast, studies conducted by Sousa et al. (2013) and Silva
et al. (2008), in patients with heart disease, showed that this indicator did not provide statistically significant measures of accuracy for the determination of IAC. This divergence of results emphasizes the importance of studying accuracy in patients with several clinical conditions with specific pathophysiological mechanisms.
High values in the measures of accuracy for the determination of IAC were also identified for the clinical indicator ineffective cough. However, data were not found in the literature to compare with these results. In the studies by Silva et al. (2008) and Silveira et al. (2008), the indicators absent cough and ineffective cough were analyzed together, preventing a comparison with the findings from this research.
In the present study, ineffective cough was defined as the inability to produce air movement, suddenly, noisy and intense, which tends to partially expel secretions from the airways. This indicator was evaluated by caregiver report and researcher observation, and then classified as present, absent, or not applicable. The ‘not applicable’ response referred to individuals who did not cough as well as individuals who did not have other signs and symptoms indicating secretions in the airways. Measures of the peak cough flow were not obtained due to the difficulty of obtaining this in children less than five years of age. However, the use of accessory muscles (abdominal and internal intercostal muscles) was observed during the assessment to identify an increased effort to expel secretions.
It is important to note that cough from high lung volume will not be effective when secretions are present primarily in peripheral airways, and other techniques are required to mobilize the secretions more centrally where cough clears the central airways of its secretions. In that way, even a child with normal respiratory muscle strength could have ineffective cough.
The indicator change in respiratory rate showed a high PVþ(83.33%), indicating a higher prob-ability of the occurrence of the diagnosis of IAC in children with this clinical indicator. The high prevalence of the diagnosis of IAC in children with ARI can influence these high predictive values. The influence from the diagnostic prevalence on measures of accuracy is described in specialized literature (Pepe, 2003; Zhou et al., 2012). In the present study, change in respiratory rate was assessed with the child awake and was based on the increase or decrease in the number of breaths over a one-minute period, taking into account the patient’s age. Children with Cheyne–Stokes respiration were eval-uated for two minutes to characterize the presence of bradypnea and/or tachypnea.
The indicator wide-eyed presented low frequency and nonsignificant measures of accuracy, as was similarly reported in the study of Silva et al. (2008). However, the results obtained by the GEE model showed that the presence of this clinical indicator increased the likelihood of children with ARI developing IAC.
However, Restrepo and Peters (2008) suggest that the presence of this clinical indicator in patients with respiratory infection is associated with more intense airway obstruction.
These results demonstrate that there are differences in measures of accuracy among the clinical indicators of IAC. The determination of the predictive capacity of these indicators increases the trustworthiness of the diagnostic inference process and allows the nurse to hypothesize regarding the most probable nursing diagnoses that represent the clinical situation presented by the patient. Unfortunately, the lack of studies in the literature with a methodological design similar to the present study limited the comparison of results. Therefore, similar studies of children with ARI should be performed to facilitate comparisons. The results may have been influenced by the incorporation and diagnostic review bias. This happens when prior knowledge about the defining characteristics is incorporated during the diagnostic inference process (Zhou et al., 2012).
Although the information presented in this research contributes to accurately diagnosing IAC in children with ARI, these results should be used with caution. The children assessed were found in specialized hospitals that served patients with a higher probability of manifesting more severe clinical conditions.
Conflict of interest
The author(s) declared no potential conflicts of interest with respect to the research, authorship, and/or publication of this article.
Funding
The author(s) received no financial support for the research, authorship, and/or publication of this article.
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