- Research article
- Open Access
Development of an algorithm to identify serious opioid toxicity in children
BMC Research Notes volume 8, Article number: 293 (2015)
The use of opioids is increasing in children; therefore, opioid toxicity could be a public health problem in this vulnerable population. However, we are not aware of a published algorithm to identify cases of opioid toxicity in children using administrative databases. We sought to develop an algorithm to identify them. After review of literature and de-identified computer profiles, a broad set of ICD-9 CM codes consistent with serious opioid toxicity was selected. Based on these codes, we identified 195 potential cases of opioid toxicity in children enrolled in Tennessee Medicaid. Medical records were independently reviewed by two physicians; episodes considered equivocal were reviewed by an adjudication committee. Cases were adjudicated as Group 1 (definite/probable), Group 2 (possible), or Group 3 (excluded).
Of the 195 potential cases, 168 (86.2%) had complete records for review and 85 were confirmed cases. The overall positive predictive value (PPV) for all codes was 50.6%. The PPV for codes indicating: unintentional opioid overdose (25/31) was 80.7%; intentional opioid overdose (15/30) was 50.0%, adverse events (33/58) was 56.9%, the presence of signs or symptoms compatible with opioid toxicity (12/47) was 25.5%, and no cases were confirmed in records from the two deaths. Of the confirmed cases, 65.8% were related to therapeutic opioid use.
For studies utilizing administrative claims to quantify incidence of opioid toxicity in children, our findings suggest that use of a broad set of screening codes coupled with medical record review is important to increase the completeness of case ascertainment.
There is a well-recognized epidemic of hospitalizations and deaths related to the increasing use of opioid analgesics in adults [1–3]. From 1999 to 2008 in the United States, rates of opioid sales, toxicity, and death related to opioid use tripled, and recent data indicate that opioid toxicity accounts for 73.8% of all deaths attributed to a prescription drug .
Although there are fewer studies in children, this vulnerable population also appears to be at high risk for opioid toxicity. A study of 960 randomly selected medical records from 12 children’s hospitals identified 107 adverse drug events with more than half attributable to opioid analgesics . Deaths have been reported in young children related to therapeutic use of codeine  and hydrocodone  in doses within or moderately exceeding recommended pediatric limits.
Despite their potential for serious adverse events, opioids are increasingly prescribed for adolescents. Opioid prescriptions for patients between 15 and 19 years of age doubled from 1994 to 2007, with estimates that opioids are prescribed in nearly 6% of ambulatory and emergency department visits made by adolescents in the US .
Given the large number of pediatric patients receiving prescribed opioids, there is an urgent need for fundamental epidemiologic studies to inform the risk–benefit decisions of prescribers and families. An essential component of these epidemiologic studies is the identification of serious adverse reactions related to opioids. Epidemiologic studies in adults have developed procedures to identify hospitalizations and deaths related to opioid use [3, 9]. However, we are unaware of similar studies in children.
Studies specifically aiming to evaluate children are important because there are significant differences between children and adults. For example, during growth and development, changes in drug metabolizing enzyme activity result in age-related differences in drug disposition . Moreover, focus on only deaths and hospitalizations is likely to underestimate the occurrence of serious adverse events in pediatric practice, given the low frequency of these events in children. Thus, the primary purpose of the present study was to develop and test procedural tools for identification of opioid toxicity in children for a broad spectrum of adverse events, including visits to emergency departments, hospital admissions, and deaths. The secondary purpose was to assess the positive predictive value (PPV) of specific groups of diagnostic codes.
We designed our procedures for large administrative databases, given their recognized utility for pharmacoepidemiology . This process included the identification of medical encounters in children likely to indicate serious opioid toxicity, procedures for adjudication of cases of possible opioid toxicity, and acquiring preliminary data on the PPV of the screening procedures as well as the circumstances of the opioid use.
Setting and study population
The study was conducted in children 2–17 years of age enrolled in the Tennessee Medicaid program between 1999 and 2011. This setting was chosen because Tennessee Medicaid included large numbers of children (49.7% of all Tennessee Medicaid enrollees) and the Medicaid files permitted efficient identification of children who filled a prescription for an opioid, potential adverse opioid effects, and pertinent demographic and clinical covariates . Study files included enrollment, pharmacy (filled prescription), outpatient and inpatient visits, as well as linked state hospital discharge (with emergency department visits) and death certificate files .
Cohort and follow-up
We sought to reduce the confounding by symptoms related to terminal illness and serious medical disorders. Therefore, we excluded children with prior medical care encounters indicating serious illnesses in the previous 12 months (including cancer, sickle cell anemia, congenital anomalies, etc.), history of organ transplant, institutional residence, and/or history of drug abuse (Table 5 in “Appendix”). For each child in the cohort and for each opioid prescription filled by that child, study follow-up included the period between the filling of the prescription and 14 days following the end of the prescribed days of supply. Although opioid toxicity most commonly occurs during current use of the drug, adverse events may delayed, or, given that opioids are often prescribed to be taken “as needed”, the period of actual use may extend beyond the dispensed days of supply.
Development study sample
Our ultimate goal is to study the epidemiology of serious opioid toxicity in a large cohort of children prescribed opioids. Our strategy for identifying serious opioid toxicity was to first identify potential cases from medical care encounters and then to confirm these by adjudication of medical records. The purpose of the current development study was to test and refine the procedures for identifying opioid-related adverse events. The development study was restricted to encounters at five major centers with a high volume of Tennessee Medicaid pediatric patients for which we had access to medical records.
Medical encounters indicating opioid toxicity
Clinical spectrum of opioid toxicity
Opioids have a wide range of adverse effects . The most serious is overdose, nearly always accompanied by respiratory or central nervous system (CNS) depression [13–15]. Other adverse effects include milder CNS effects, constipation, nausea, vomiting, dermatologic reactions, urinary retention, myoclonus, seizures (with meperidine) and metabolic disorders [12, 14, 16].
Encounters indicating potential cases of opioid toxicity
Serious opioid toxicity was defined as Group 1: definite/probable, or Group 2: possible based on medical record review. Encounters of interest were restricted to emergency department visits, hospital admissions, and deaths. Potential cases were identified from ICD-9-CM diagnostic codes, either primary or secondary, recorded for the encounter.
There were four groups of codes. First, were the external cause of injury codes that indicate medication poisoning/overdose (Table 6 in “Appendix”). Because all cohort follow-up consisted of either current or very recent use of an opioid, we hypothesized there was a considerable prior probability of opioid involvement in an adverse drug reaction. Thus, in this development study, we included codes that indicated an opioid or unspecified analgesic (codes in Group A of tables) as well as those that indicated an unspecified medication (codes in Group C of the tables), unless the encounter also indicated a specific drug that was not an opioid (codes in Group B). We did not consider encounters with other specified medications, because, given that the reaction had been attributed to another drug (e.g., hypoglycemia related to insulin), we thought it would be unlikely to be adjudicated as due to an opioid. Second, were the external cause of injury codes indicating an adverse effect in therapeutically appropriate use (Table 7 in “Appendix”). Third, were diagnosis codes indicating symptoms of the most serious opioid toxicity: respiratory depression and adverse CNS effects (Table 8 in “Appendix”), even in the absence of an external cause of injury code. Finally, records for all deaths during follow-up were reviewed, regardless of the cause of death diagnosis codes.
There were several other groups of codes initially considered but ultimately not included in those for identifying potential cases. These included diagnoses indicating symptoms possibly due to less serious toxicity (such as rash, nausea, or constipation) in the absence of a code indicating an adverse drug effect. These were excluded because of the large number of such encounters and the difficulty of attributing them to an opioid even with medical record review. We also excluded some less specific codes for respiratory and CNS symptoms (e.g., dizziness), based on their relative commonness, difficulty of attribution to an opioid, analysis of computer profiles, and preliminary analysis of the development study data. We initially considered symptoms related to metabolic disorders, but preliminary analysis suggested these were infrequent and had poor PPV. We also considered administration of naloxone as an indicator of overdose, but a preliminary review indicated that naloxone was most frequently used to reverse the effects of opioid administration following a surgical procedure. However, naloxone use did not trigger exclusion from the cohort.
After de-identification, all medical records were independently reviewed and adjudicated by two study physicians (STC and CPC) using the study instrument (Figure 1 in “Appendix”). Episodes for which there was disagreement among adjudicators were subsequently adjudicated by all the investigators. Following standard procedures, we reviewed complete medical records for evidence of symptoms and signs clearly attributed to opioid toxicity with no other process implicated. Other clinical information included temporal sequence of events, medical interventions, escalation of care and evidence of symptoms or signs attributable to other causes. Consensus was reached after discussion of all available evidence.
Adjudicated episodes were classified into one of the following mutually exclusive categories:
Group 1: Definite/Probable opioid toxicity There were two scenarios:
The presence of both of the following criteria: (1) signs and symptoms compatible with opioid toxicity and attributed by the treating physician as related to an opioid poisoning, overdose or adverse event; and (2) no other drug or disease process implicated in the presence of these signs or symptoms.
Direct intervention or escalation of care because of potential opioid toxicity (for example: admission to the Intensive Care Unit after inadvertent overdose of hydrocodone).
Group 2: Possible opioid toxicity These episodes met both of the following criteria: (1) signs or symptoms compatible with opioid toxicity that were not clearly attributed directly to opioid toxicity but not attributed to other causes; and (2) the temporal sequence suggested that opioid use was a possible cause of signs or symptoms.
Group 3: excluded, opioid toxicity unlikely There were three scenarios in which opioid toxicity was excluded:
Presence of signs or symptoms compatible with opioid toxicity but attributed to other causes (for example: vomiting attributed to gastrointestinal infection by treating physician).
Presence of signs and/or symptoms compatible with, but not clearly attributed to opioid toxicity (but not attributed to other causes either); and lack of a temporal sequence suggesting that opioids were a possible cause of signs or symptoms.
Neither signs nor symptoms compatible with opioid toxicity nor escalation of care because of potential opioid toxicity.
Our definition did not consider findings from urine and serum drug screens for opioids. These were not consistently performed and have been shown to have limited utility in the diagnosis of acute opioid toxicity .
Severity of the outcome
Cases that met the criteria for probable or possible opioid toxicity were classified according to severity of the event:
Death: attributed to opioid.
High: the adverse effect resulted in hospitalization or escalation of care or management.
Intermediate: the opioid-related symptoms were the primary reason for an emergency room visit.
Low: the opioid-related symptoms were an incidental or minor part of the encounter.
For each probable or possible case, we also recorded both the circumstances of the opioid exposure as well as the source of the opioid. The circumstances of exposure included: (1) self-harm—any indication of attempted suicide or intentional overdose, (2) recreational ingestion, (3) unintentional overdose—e.g., parent inadvertently administered an extra dose, (4) therapeutic use—the medication was taken as prescribed, (5) opioid withdrawal, (6) unspecified—no indication of circumstances or intent documented. The source of the opioid related to the adverse event was: (1) the patient’s prescription, (2) another person’s prescription, (3) an illegal source, or (4) not specified.
Statistical analyses were conducted in two steps. First, tables were constructed specifying whether clinical criteria for opioid toxicity (definitive, probable and possible) were met according to review of medical records and PPVs were calculated. Secondary analyses included calculation of PPV according to time elapsed since the end of the days of supply (through 7 days and 8–14 days).
Cases adjudicated as Group 1 (definite/probable) or Group 2 (possible) opioid toxicities were further classified by severity and by exposure, as detailed above. Second, based on final adjudication, positive predictive values were calculated. Reliability was expressed as kappa statistics, excluding 12 initial cases used to refine the adjudication procedures. Analyses were conducted with the use of STATA 12 (StataCorp. 2011. Stata Statistical Software: Release 12, College Station, TX: StataCorp LP).
The study was approved by the Institutional Review Board at Vanderbilt University and the Tennessee Medicaid program.
Demographic of study population
Based on the screening codes (listed in the “Appendix”), 195 potential cases of opioid toxicity in children from five hospitals in Tennessee were identified. These children were 11.3 ± 5.0 years old on average and predominantly Caucasian (59%) and female (57%).
Positive predictive value
From the 195 potential cases, records for four cases (2%) did not have enough information to adjudicate and 23 (12%) were not found. Of the 168 remaining potential cases, 85 were adjudicated as Group 1 (definite/probable) or Group 2 (possible) opioid toxicity event (PPV = 50.6%) (Table 1).
We calculated PPVs for specific diagnostic codes. Of 31 potential cases identified as unintentional poisoning/overdose, 25 were confirmed (PPV = 80.7%). Thirty-three of the 58 cases identified based on codes for adverse effect of drugs in therapeutic use were confirmed, with a PPV = 56.9%. Lower PPVs were found for patients with codes indicating intentional overdose (PPV = 50.0%), or symptoms compatible with opioid toxicity (25.5%). Although the numbers were small, cases identified on the basis of CNS symptoms had a PPV = 28.1%. The PPV for cases identified based on respiratory symptoms was lower (20.0%) (Table 2). There were two deaths, but after review of records the causes of death in both cases were not compatible with opioid toxicity.
We calculated the PPVs according to the time elapsed since the end of the days of supply (Table 3). There were 121 cases identified between the filling of the prescription and 7 days following the end of the days of supply, of which 69 were confirmed, with a PPV = 57.0%. Of the potential 47 potential cases identified 8–14 days after the end of the days of supply, 16 were confirmed (PPV = 34.0%).
Severity of outcome, intent, and source of the opioid
With regard to the severity of the outcomes, 27 (31.8%) cases were classified as high, 52 (61.2%) as intermediate, and six (7.1%) as low severity. Based on intent of opioid use, 56 (65.8%) cases were related to therapeutic use, 10 (11.8%) to self-harm, nine (10.6%) to unintentional overdose, and four (4.7%) to recreational use of opioids. There was one case with records indicating opioid withdrawal and in six cases (7.1%) it was not possible to determine the intent. We also assessed the source of opioid. The majority of the cases (n = 76, 89.4%) had records supporting the use of a prescribed opioid, while the use of another person’s prescription was noted in only four cases. There were no cases with indication of an illegal source and in six cases (7.1%) it was not possible to specify the source (Table 4).
All cases were initially reviewed by two clinicians. From the 156 cases available for estimation of inter-rater reliability, 13 cases were brought to the adjudication committee for further discussion. There was agreement in 91.7% (the expected agreement was 50.6%) and the kappa statistics was 0.83 (p < 0.001). In eight of these 13 cases, one reviewer initially adjudicated the case as Group 2 (possible) and the other as Group 3 (exclusion).
To the best of our knowledge, this is the first study describing the development and validation of a procedural tool, based on identification of potential cases with ICD codes and adjudication of individual cases with review of medical records, to identify opioid toxicity in children for use in pharmacoepidemiologic studies in automated databases. Our analyses showed that the study codes for identifying adverse opioid effects had a low PPV, which suggests that review of medical records is important.
Many symptoms of opioid toxicity have a broad differential diagnosis and may be related to other concurrent factors, including other medications . Furthermore, it is well recognized that medications affect children and adult differently. Although others have developed procedures to identify fatal cases of opioid overdose from diagnosis codes , these results are not necessarily applicable to non-fatal outcomes. Furthermore, we cannot assume that data from adults are necessarily applicable to children.
Thus, we identified a set of screening codes for opioid toxicity specifically for a pediatric population. To adjudicate potential cases, we followed a detailed procedure that began with confirming the presence of symptoms or signs compatible with opioid toxicity. We excluded cases in which the treating physician attributed the symptoms and signs to other causes. The temporal sequence of events and intervention/escalation of care were also considered. The initial complete review of each medical record and its adjudication were done by two experienced physicians, blinded to the other’s adjudication. Although the interrater reliability kappa of 0.84 indicates substantial agreement ; there were 7.7% cases in which the reviewers disagreed. Thus, our adjudication process should improve accuracy relative to review and adjudication by a single investigator.
Although the overall PPV was low, PPVs differed greatly according to the type of diagnosis. Cases that were identified based on codes indicating opioid or analgesic unintentional overdose/poisoning had the highest PPV; but they only accounted for 25 of the 85 (29.4%) confirmed cases. This suggests that studies to quantify the incidence of opioid adverse effects should not be limited to these codes. In contrast, cases identified based on diagnosis codes consistent with symptoms of opioid toxicity, but with no mention of a drug, had a PPV of only 25.5%. However, such cases accounted for 12 (14.1%) of the confirmed cases. Therefore, failure to use symptom-related codes will lead to underestimation of the incidence of opioid toxicity.
Several limitations should be considered. First, determination of causality was based primarily on the judgment of the treating physician, as documented in the medical records. This limitation, inherent to retrospective studies, may be particularly important for less serious opioid adverse effects with multiple causes, such as dermatologic or gastrointestinal reactions. Second, the algorithm was developed to identify cases of opioid toxicity related to hospitalization or an emergency department visit; thus, less serious events were not captured. Third, because the present study is restricted to children with a filled opioid prescription, our procedures are designed for study of therapeutic use of opioids. Fourth, 11.8% of records, primarily from early years, were unavailable for review, most commonly because the records were already destroyed. Fifth, we do not include data on treatment duration. Finally, the study was conducted in children enrolled in Tennessee Medicaid, and because our primary area of concern was relatively healthy children receiving opioids therapeutically we exclude children with serious conditions, which may limit generalizability to other databases and clinical settings.
In summary, the overall positive predictive value of diagnosis codes indicating opioid toxicity was low. Our findings suggest that for incidence studies, a two-step process would allow inclusion of a broader range of screening diagnostic codes and thus would capture a larger fraction of cases of opioid toxicity in the study population.
central nervous system
International Classification of Diseases
positive predictive value
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CPC, STC, WOC, KTM, CMS, and WAR participated in the study design. CPC, STC, WOC, KTM, KH, JAD, CMS, and WAR participated in the analysis and interpretation of data. CPC and WAR drafted the manuscript. STC, WOC, KTM, KH, JAD, and CMS revised the manuscript critically and contributed to the final version. All authors read and approved the final manuscript.
This study was supported by Grants from the National Institute for Child Health and Human Development (HD074584), the National Institute for Arthritis and Musculoskeletal and Skin Diseases (P60AR056116 and K23AR064768) and a Vanderbilt Physician Scientist Development Award. We gratefully acknowledge the Tennessee Bureau of TennCare and the Department of Health, which provided study data. We are indebted to Shannon M. Stratton, BS; Leanne Balmer, RN; and Michelle DeRanieri, RN, who assisted with medical records abstraction.
Compliance with ethical guidelines
Competing interests The authors declare that they have no competing interests.