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Abstract

Introduction:

Migraine is a common, disabling chronic pain condition possibly related to changes in endothelial and vascular structure and function. Several observational studies have suggested an elevated risk of cervical artery dissection (CeAD) in patients with a history of migraine. We aimed to investigate this potential association using systematic review and meta-analytic methods.

Patients and methods:

We utilized a pre-defined search protocol to identify and screen studies related to migraine and CeAD in PubMed, Embase, and the Web of Science Core Collection. We assessed the risk of bias and performed a meta-analysis of selected studies to assess the association between migraine and CeAD. We also performed subgroup analyses by migraine subtype, biological sex, and the use of stroke versus non-stroke controls.

Results:

We identified 11 studies (N = 9857 patients) for inclusion in the meta-analysis. Meta-analysis showed an association between migraine and CeAD with an odds ratio of 1.74 (95%CI 1.38–2.19). There was high heterogeneity among the included studies (I² = 61%). Publication bias was present but the Trim-Fill imputation suggested that the impact on results was likely minimal. Subgroup analyses revealed an association between migraine without aura and CeAD (OR 1.86, 95%CI 1.55–2.24) but not migraine with aura and CeAD (OR 1.15, 95%CI 0.71–1.88). There was no difference in the association between migraine and CeAD in men compared to women.

Discussion and conclusion:

A history of migraine is associated with an increased risk of CeAD. Further studies are needed to elucidate the potential pathophysiologic mechanisms underlying this association.

Keywords

Migraine cervical artery dissection stroke

Introduction

Migraine affects approximately one billion people worldwide and is the leading cause of years lived with disability in individuals younger than 50 years.¹ Approximately one-third of individuals with migraine suffer from migraine with aura, characterized by transient neurological symptoms preceding a migraine attack.² Recent observational studies have indicated that migraine, particularly migraine with aura, is associated with an increased risk of ischemic stroke.^3–5 A prior meta-analysis found that the association between migraine and stroke was the strongest among those aged <45 years.⁴ However, the biological mechanisms underlying this association remain unclear.

Cervical artery dissection (CeAD) is an intimal tear in a cervical artery’s wall (i.e. carotid or vertebral artery) and is the most common reason for ischemic stroke in young and middle-aged adults.^6–8 Although the etiology of spontaneous CeAD is not fully understood, research has suggested both genetic factors and vascular conditions such as hypertension and migraine could be risk factors for CeAD.⁶

A prior meta-analysis observed an over two-fold increase in the risk of CeAD for individuals with migraine.⁹ However, only five studies, all of fairly small size, were included in the meta-analysis. Since the publication of this meta-analysis, several additional studies, including larger-scale studies, have been published providing the opportunity to answer further questions, such as whether the association depends on migraine subtypes and the presence of stroke, both of which are clinically and etiologically important. We aim to provide an updated systematic review and meta-analysis of the association between migraine and CeAD and explore if this association varies by aura status, sex, and use of stroke versus non-stroke controls.

Methods

This study followed the Preferred Reporting Items for Systematic reviews and Meta-Analyses (PRISMA) guidelines.¹⁰

Data sources and searches

We searched PubMed, Embase, and Web of Science Core collection from database inception to August 2, 2022. We used the following search terms: (“migraine” OR “migraine disorders” OR “migrain*”) AND (“cervical dissection” OR “cervical artery dissection” OR “vertebral artery dissection” OR “vertebrobasilar artery dissection” OR “basilar artery dissection” OR “carotid artery, internal, dissection” OR “carotid artery injury” OR “artery dissection” OR “arterial dissection” OR “arterial tear” OR “intimal tear”) (Supplemental Table S1). We conducted reference mining of existing systematic reviews, meta-analyses, and relevant primary studies to identify additional literature.

Study selection

We included case-control, cohort, and cross-sectional studies that provided sufficient information to calculate a measure of association. Studies with case-report or case-series designs and conference abstracts were excluded. For the exposure, we recorded whether the study assessed active migraine or history of migraine, including self-reported diagnosis or medical diagnosis of migraine according to the International Classification of Headache Disorders (ICHD) (⩽3rd edition) criteria,¹¹ or the International Classification of Diseases (ICD) 9th or the ICD 10th revision^12,13 for the outcome, we required studies to investigate participants with dissection of one or more cervical arteries, including carotid, vertebral, or basilar arteries with ascertainment of the dissection by direct visualization techniques, including angiography, duplex scan, magnetic resonance imaging, or computerized tomography. We excluded studies that investigated hereditary CeAD or major traumatic CeAD. Study selection was performed with a semi-automated software (Covidence, Veritas Health Innovation Ltd, Melbourne, Australia). Independent pairs of reviewers completed the title and abstract screen as well as the full-text screen. Any disagreement was resolved by a third investigator.

Data extraction and quality assessment

Extracted information included first author, publication year, study design, population description, sample size, mean age and its standard deviation, diagnostic criteria for migraine, migraine subtypes, diagnostic tools for CeAD, matching factors, covariates, effect estimates from the main and subgroup analyses, and their associated 95% confidence intervals. We applied the Newcastle-Ottawa Scale (NOS) to evaluate the quality of the selected studies with a maximum of 9 points.¹⁴

Statistical analysis

Odds ratios (ORs) were chosen as the primary measure of association and multivariable-adjusted ORs were used in the analyses when provided. If adjusted ORs were not provided, we calculated a Mantel-Haenszel weighted OR if the study included sufficient information for univariable adjustment. Otherwise, we included an unadjusted OR. A random-effects restricted maximum likelihood (REML) model was used to allow high between-study variability. We performed the Cochran’s Q test and calculated the I² statistic to quantify heterogeneity¹⁵ and used the Galbraith plot to visualize the degree of heterogeneity and adequacy of the random-effects model.¹⁶ We assessed publication bias via the Begg’s test¹⁷ and Egger’s test.¹⁸ We then quantified the magnitude of potential publication bias using the Trim and Fill method with the linear estimator¹⁹; we visualized the result in a funnel plot.

We performed three pre-specified subgroup analyses based on sources of heterogeneity that we anticipated a priori due to differences in migraine subtypes (migraine with aura [MA] versus migraine without aura [MO]), sex, and control group selection (stroke vs non-stroke controls). The Cochran’s Q test (Q_b) with 1 degree of freedom was used to assess the between-group difference for each subgroup analysis.

Three sensitivity analyses evaluated the robustness of the results. First, we performed a leave-one-out test to assess the impact of each study on the pooled estimate. Second, during the full-text screening, we identified two publications with overlapping study populations. In the primary analysis, we only included the study which reported adjusted ORs. In a sensitivity analysis, we replaced this study with the one that only provided unadjusted ORs. Third, for studies in which we calculated Mantel-Haenszel weighted ORs, we exchanged these estimates with the unadjusted ORs and re-computed the pooled result. For all analyses, we set the significance level to an alpha of 0.05, two-sided. All analyses were performed using Stata version 17 (Stata, College Station, TX, USA).

Results

Identification of studies

The study selection process is summarized in Figure 1. We identified 237 studies from PubMed, 516 studies from Embase, and 296 from the Web of Science Core Collection. After removal of duplicates, 707 studies were screened. After screening titles and abstracts, we excluded 649 studies irrelevant to the study topic and selected 58 studies for the full-text review. The inter-rater reliability had a $κ$ value of 0.49 for the title and abstract screen. In the full-text review, 46 studies were excluded; 11 were included in the main analysis; 1 was included in the sensitivity analysis described above. The $κ$ statistic was 0.86 for the full text review. Reasons for exclusion of studies are detailed in Figure 1. Two studies had an overlapping study population.^20,21 We chose to include the Pezzini et al.²¹ paper in the main analysis and used the Pezzini et al.²⁰ paper for sensitivity analysis because it did not report an adjusted OR.

Figure 1.

Flowchart of study selection.

Study characteristics

In the main analysis, we included 11 case-control studies (Table 1). The sample size of the individual studies ranged from 45 to 4055 participants. Seven studies included sufficient information on migraine subtypes and five studies presented sufficient data on sex to allow for subgroup analyses by these factors. All 11 studies provided criteria for control selection; notably, the type of control groups varied across studies. Three studies compared cases to healthy controls.^22–24 One study compared cases to hospitalized patients who had cervical vascular imaging but did not have stroke.²⁵ We categorized these four studies into the subgroup of non-stroke controls.^22–25 Six studies compared CeAD cases to patients who had ischemic stroke unrelated to CeAD.^26–31 One study compared cases to two separate control groups – healthy controls as well as patients with non-CeAD induced stroke.²¹ For this study, we included the stroke controls since they were more likely to resemble cases and thus reduce residual confounding. These seven studies were categorized into the subgroup of stroke controls.^21,26–31

Table 1.

Characteristics of studies investigating the association between migraine and cervical artery dissection.

Study	Population description	Sample size	Mean age (SD)	CeAD diagnosis	Migraine diagnosis	Migraine subtypes	Matching factors	Multivariable adjustment
D’Anglejan-Chatillonet al.²³	Cases: CeAD patients Controls: relatives or friends	Cases: 50 Controls: 100	Cases: 42.1 (8.6) Controls: 43.6 (9.1)	Conventional angiography or DSA	ICHD-1	Any MA MO	Sex, age	No
Tzourioet al.²⁷	Cases: CeAD patients Controls: patients with a cerebral ischemic event other than CeAD	Cases: 47 Controls: 52	Cases: 44.8 (7.4) Controls: 45.8 (8.5)	Conventional angiography or DSA; MRI/MRA; Duplex	ICHD-1; Direct interview	Any MA MO	Sex, age ±5 years	Sex, age, medical center, body mass index, level of education
Akova-Öztürk²²	Cases: CeAD patients Controls: relatives; friends, hospital staff	Cases: 148 Control: 148	Cases: 42.6 (10.7) Controls: 42.7 (10.8)	MRI; medical history	ICHD-1; questionnaire-based	AnyMA MO	Sex, age ±1 year	No
Pezzini et al.²¹	Cases: patients with CeAD; Stroke controls: patients with first-ever non-CeAD related acute ischemic stroke occurring age <45; Healthy controls: hospital staff with no known history of vascular diseases and aged <45	Cases: 72 Stroke controls: 72 Healthy controls: 72	Cases: 43.6 (11.1) Stroke controls: 42.9 (11.1) Healthy controls: 43.0 (10.8)	Conventional angiography or DSA; MRI/MRA; Duplex	ICHD-1; Direct interview	Any MA MO	Sex, age	Sex, age, medical center, hypertension, smoking status, obesity
Pezzini et al.,*²⁰	Cases: patients with CeAD Stroke controls: patients with first-ever non-CeAD related acute ischemic stroke occurring age <45 Healthy controls: hospital staff with no known history of vascular diseases and aged <45	Cases: 106 Stroke controls: 227 Healthy controls: 187	Cases: 42.9 (10.2) Stroke controls: 34.9 (7.8) Healthy controls: 36.4 (7.5)	Conventional angiography or DSA; MRI/MRA; Cervical ultrasound/duplex	ICHD-1; Direct interview	AnyMA MO	Sex, age ±3 year, geographic area, ethical background	No
Artto et al.²⁴	Cases: CeAD patients Controls: healthy individuals linked via registry	Cases: 313 Control: 313	Cases: 46.1 Controls: 45.8	DSA; MRI/MRA; CTA; ultrasound³¹	ICHD-2 plus the Finnish migraine-specific questionnaires for family studies	Any MA MO	Sex, age ±5 years	Sex, age, oral contraceptives, hypertension, diabetes, and current smoking
Metso et al.²⁶	Cases: CeAD patients with stroke Controls: non-CeAD ischemic stroke patients	Cases: 635 Controls: 653	Cases: 43.9 (10.0) Controls: 44.5 (10.5)	Conventional angiography or DSA; MRI/MRA; CTA; ultrasound	ICHD-2	AnyMA MO	Sex, age ±5 years, medical center	Sex, age, country of inclusion, prospective/retrospective inclusion, hypertension, current smoking, hypercholesterolemia, diabetes, BMI, use of oral contraceptives or hormone replacement therapy in women
Zhou et al.²⁵	Cases: patients with spontaneous vertebral artery dissection Controls: patients underwent DSA at the same hospital without CeAD, stroke, or aneurysm	Case: 112 Control: 224	Cases: 41.1 (9.0) Controls: 40.9 (9.9)	Conventional angiography or DSA; MRI/MRA; CTA; Duplex	Not specified	Any	Sex, age ±5 years	Hyperhomocysteinemia, smoking, trivial trauma, infection⩽4 weeks prior to vascular event, connective tissue/vascular disorders, vertebral artery hypoplasia
Thomas et al.²⁸	Cases: CeAD patients aged ⩽55 Controls: non-CeAD ischemic stroke patients age ⩽55	Cases: 24 Controls: 21	Cases: 43.8 (8.8) Controls: 39.1 (11.5)	MRI; CTA	Medical diagnosis; self-report; on medication for migraine³²	Any	Sex, age	No
von Sarnowski et al.²⁹	Cases: CeAD patients Controls: non-CeAD patients with cerebrovascular events	Cases: 374 Controls: 3681	Aged from 18 to 55 (mean age not available)	MRI/MRA; CTA; Duplex	ICHD-2³³	Any	No	No
De Giuli et al.³¹	Cases: CeAD caused ischemic stroke patients aged 18–45 Controls: non-CeAD caused ischemic stroke patients aged 18–45	Cases: 334 Controls: 2151	Cases: 37.4 (6.8) Controls: 36.7 (7.1)	Conventional angiography; MRI/MRA; CTA	ICHD-1&2 or earlier; Direct interview	Any MA MO	No	Sex, age, hypertension, diabetes, smoking, hypercholesterolemia
Garg et al.³⁰	Cases: CeAD patients aged 15–45 Controls: non-CeAD patients with acute ischemic stroke aged 15–45	Cases: 79 Controls: 254	Cases: 34.9 (6.7) Controls: 36.9 (7.2)	DSA; MRI/MRA; CTA of the brain and neck	Medical history	Any	No	No

CeAD: cervical artery dissection; DSA: digital subtraction angiography; ICHD: International Classification of Headache Disorders; MA: migraine with aura; MO: migraine without aura; MRI: magnetic resonance imaging; MRA: magnet resonance angiography; CTA: computerized tomography angiography.

Overlapping population with Pezzini et al.²⁰

All 11 studies ascertained the outcome using cervical imaging techniques, including angiography, computed tomography (CT), magnetic resonance imaging (MRI), and duplex ultrasound. There were variations in the ascertainment of migraine status. Eight studies assessed migraine history before CeAD or stroke occurrence.^{21,22,24,26,27,29–31} One study asked the participants to recall their migraine status as of the time of dissection.²³ Two studies did not specify whether history of migraine prior to dissection or active migraine at the time of dissection was ascertained.^25,28 Eight studies assessed migraine according to guidelines of the International Classification of Headache Disorders (ICHD).^{21–24,26,27,29,31} Two studies relied on self-reported diagnosis or medical records with unspecified criteria.^27,29 One study did not provide information on how migraine was ascertained.²⁵

We directly obtained the adjusted OR from six studies.^{21,24–27,31} We computed the univariable-adjusted OR for two studies using Mantel-Haenszel weights by sex.^23,29 We calculated the crude OR for three studies.^22,28,30 For the selected studies, the overall quality of the evidence was moderate, with the NOS scores ranging from 4 to 7 points (Supplemental Table S2).

Results from meta-analysis

There were 2188 CeAD cases and 7669 controls identified from the 11 selected studies; 713 (32.6%) of the cases had migraine while 1867 of the controls (24.3%) had migraine. Meta-analysis showed a positive association between migraine and cervical artery dissection (OR 1.74, 95%CI 1.38–2.19; Figure 2). Heterogeneity among studies was high (I² = 60.73%, p = 0.01). The Galbraith plot showed that all studies fell within the 95% confidence interval of the pooled OR except for the von Sarnowski et al. study (Supplemental Figure S1).²⁹ The presence of publication bias was suggested by the Egger test (p = 0.003) and the Begg test (p = 0.020). The funnel plot also showed moderate asymmetry (Supplemental Figure S2). However, the pooled OR was only slightly attenuated toward the null after the imputation of three small studies (OR 1.56, 95%CI 1.23–1.99). This result indicated that the overall pooled estimate was not significantly impacted by the potential publication bias.

Figure 2.

Forest plot showing the meta-analysis of 11 studies.

Subgroup analysis based on migraine type showed that migraine without aura was significantly associated with CeAD (OR 1.86, 95%CI 1.55–2.24, I² = 0.00%) but migraine with aura was not (OR 1.15, 95%CI 0.71–1.88, I² = 66.77%; Figure 3). Migraine was significantly associated with CeAD among both men (OR 1.55, 95%CI 1.25–1.92, I² = 12.80%) and women (OR 1.35, 95%CI 1.10–1.66, I² = 10.74%) and the strength of the association did not differ significantly by sex (p = 0.37; Figure 4). The association between migraine and CeAD was observed whether the studies used non-stroke controls (OR 1.78, 95%CI 1.18–2.69, I² = 49.29%) or stroke controls (OR 1.77, 95%CI 1.29–2.42, I² = 71.09%) and the strength of the association was similar regardless of the control group used (p = 0.98; Figure 5). The results from our sensitivity analyses were consistent with those from the main analyses (Supplemental Figures S3, S4, and S5).

Figure 3.

Forest plot showing the meta-analyses by migraine subtypes.

Figure 4.

Forest plot showing the meta-analyses by men and women.

Figure 5.

Forest plot showing the meta-analyses by control selection.

Discussion

Our meta-analysis shows that having a history of migraine is associated with 1.74-fold increased odds of CeAD. Consistent with a prior meta-analysis on migraine and CeAD,⁹ this association was primarily driven by individuals with migraine without aura. In contrast, we observed no association between migraine with aura and CeAD, although significant heterogeneity between studies was observed. The finding of an association between CeAD and migraine without aura but not migraine with aura is intriguing as migraine with aura is a stronger risk factor for ischemic stroke and is therefore thought to have more shared vascular pathology.³⁵

The prior meta-analysis on migraine and CeAD had limited ability to explore potential effect modification by factors such as sex. Although some studies have suggested that the migraine-stroke association may be strongest among young women,⁴ we observed similar associations between migraine and CeAD among both men and women. Unfortunately, we were unable to further explore whether age could modify the relationship between migraine and CeAD, because most included studies enrolled younger stroke patients with mean age ranging from 36 to 47 years old.

Both non-CeAD ischemic strokes and ischemic strokes secondary to CeAD have been associated with a history of migraine.^9,35 Thus, we anticipated that using non-CeAD stroke patients as controls rather than controls derived from the healthy population, might underestimate the strength of the association between migraine and CeAD. However, subgroup analyses did not reveal any significant differences when CeAD patients were compared with individuals with no history of stroke or patients who had experienced a non-CeAD-related stroke. Limited by sample sizes, we were unable to stratify by both migraine aura status and the type of control group used. Given that there is a stronger association between migraine with aura and ischemic stroke than between migraine without aura and ischemic stroke,³⁶ the use of controls with a history of stroke may be one reason for the lack of association between migraine with aura and CeAD.

Recent genetic analyses have suggested that common genetic factors related to the vascular structure and function underly both migraine and CeAD. A genetic correlation study on pairwise traits identified AMAMTSL4/ECM1, PLCE1, and MRVI1 as new candidate genes implicated in the susceptibility to both migraine and CeAD.³⁷ The study also confirmed shared loci between migraine and CeAD at PHACTR1/EDN1, LRP1, and FHL5, which had been identified in a prior genome-wide association study on CeAD.³⁸ The observed genetic correlation was primarily driven by the migraine without aura subtype; however, the lack of genetic instruments for the migraine with aura subtype may have made this study underpowered to detect any correlation between migraine with aura and CeAD if it exists. Furthermore, the authors found an odds ratio of 1.69 (95%CI 1.24–2.3) for CeAD per doubling migraine prevalence using Mendelian randomization techniques. Their findings were consistent with not only our result in the primary analysis but also the differences by aura status in the subgroup analysis.

Strengths of this study include the use of three extensive databases to identify the 11 included studies. Additionally, most included studies had moderate to high quality (NOS ⩾ 4). Furthermore, we performed pre-planned subgroup analyses by aura status, sex, and the use of stroke controls to further understand the association between migraine and CeAD and potentially identify subgroups who are at most risk of CeAD. Nevertheless, several limitations remain. First, we found relevant publication bias indicating a shortage of small negative studies. However, the imputation of three studies assumed to be missing did not substantially change the pooled effect estimate. Second, the studies included in the primary analysis showed high heterogeneity (I² = 60.73%). In addition to using the random-effects model to account for heterogeneity, we also examined heterogeneity within each subgroup to identify potential sources of heterogeneity. It is likely that the overall heterogeneity is primarily driven by the within group differences for the migraine with aura subtype and the control selections. A potential source of heterogeneity that we were unable to systematically investigate was the differences in the adjustments made for confounding among individual studies. Third, some studies asked participants to retrospectively report their migraine status, including migraine aura status, prior to the index event or study enrollment which may result in recall bias. However, this bias may not substantially affect the results since the use of stroke comparators made both cases and controls equally likely to recall migraine episodes. Fourth, studies often did not provide detailed information on how migraine aura was assessed and did not provide information on specific migraine aura features. It is possible the differences in migraine aura features or differences in the method of diagnosing migraine aura may underlie the high heterogeneity seen in this subgroup. Future studies with detailed migraine phenotype information will be needed to determine which migraine features are most likely to increase the risk of CeAD.

While we were able to perform some subgroup analyses to address specific gaps in knowledge, unanswered questions remain. For example, none of the included studies reported the frequency of migraine attacks, the severity of the headaches, details about the aura presentation, other migraine subcategories (i.e. hemiplegic migraine), or the use of preventative or abortive medications for migraine treatment. Areas of interest for future investigation would be whether the risk of CeAD or ischemic stroke is modifiable by use of preventative or abortive headache medications which decrease migraine frequency or duration of migraine attacks. Triptan use is of particular interest, since triptans have been linked to cardiovascular events and are the first line treatment for migraine headaches refractory to simple analgesics.³⁹ However, a large case-control study found no increase in all-cause stroke or cardiovascular death in migraine patients who were prescribed triptans compared to those who were not.⁴⁰

In conclusion, this study strengthens the evidence that history of migraine, and particularly migraine without aura, is associated with CeAD risk. Further investigations need to understand whether the use of migraine medications may modify this association, and to identify other modifiable risk factors to lower the risk of CeAD among individuals with migraine, and to explore if screening strategies may be beneficial in this population.

Supplemental Material

sj-docx-1-eso-10.1177_23969873231191860 – Supplemental material for Migraine and the risk of cervical artery dissection: A systematic review and meta-analysis

Supplemental material, sj-docx-1-eso-10.1177_23969873231191860 for Migraine and the risk of cervical artery dissection: A systematic review and meta-analysis by Zihan Sun, Julian Kleine-Borgmann, Joome Suh, Gregory C McDermott, Anastasia Vishnevetsky and Pamela M Rist in European Stroke Journal

Supplemental Material

sj-docx-2-eso-10.1177_23969873231191860 – Supplemental material for Migraine and the risk of cervical artery dissection: A systematic review and meta-analysis

Supplemental material, sj-docx-2-eso-10.1177_23969873231191860 for Migraine and the risk of cervical artery dissection: A systematic review and meta-analysis by Zihan Sun, Julian Kleine-Borgmann, Joome Suh, Gregory C McDermott, Anastasia Vishnevetsky and Pamela M Rist in European Stroke Journal

Footnotes

Acknowledgements

None.

Declaration of conflicting interests

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.

Informed consent

Given that this study was a meta-analysis of previously published studies and data from those studies, we did not seek IRB approval for our analysis. The original manuscripts describe the process of obtaining patient consent.

Ethical approval

Guarantor

Dr. Kleine-Borgmann and Ms. Sun take full responsibility for the data.

Contributorship

ZS & JKB: study conception and design, data extraction and analysis, drafted the manuscript and figures; JS & GCM & AV: study conception and design, data extraction and analyses, drafted the manuscript and figures; PMR: study design; data analyses and interpretation; revision of the manuscript for intellectual content; provided supervision.

ORCID iD

Pamela M Rist

Supplemental material

Supplemental material for this article is available online.

References

Steiner

Stovner

Vos

, et al. Migraine is first cause of disability in under 50s: will health politicians now take notice? J Headache Pain 2018; 19: 4.

Lipton

Scher

Kolodner

, et al. Migraine in the United States: epidemiology and patterns of health care use. Neurology 2002; 58: 885–894.

Kurth

Winter

Eliassen

, et al. Migraine and risk of cardiovascular disease in women: prospective cohort study. BMJ 2016; 353: i2610–292.

Schürks

Rist

Bigal

, et al. Migraine and cardiovascular disease: systematic review and meta-analysis. BMJ 2009; 339: b3914.

Mahmoud

Mentias

Elgendy

, et al. Migraine and the risk of cardiovascular and cerebrovascular events: a meta-analysis of 16 cohort studies including 1 152 407 subjects. BMJ Open 2018; 8: e020498.

Debette

. Pathophysiology and risk factors of cervical artery dissection: what have we learnt from large hospital-based cohorts? Curr Opin Neurol 2014; 27: 20–28.

Gottesman

Sharma

Robinson

, et al. Clinical characteristics of symptomatic vertebral artery dissection a systematic review. Neurologist 2012; 18: 245–254.

Debette

Leys

. Cervical-artery dissections: predisposing factors, diagnosis, and outcome. Lancet Neurol 2009; 8: 668–678.

Rist

Diener

Kurth

, et al. Migraine, migraine aura, and cervical artery dissection: a systematic review and meta-analysis. Cephalalgia 2011; 31: 886–896.

10.

Page

McKenzie

Bossuyt

, et al. The PRISMA 2020 statement: an updated guideline for reporting systematic reviews. BMJ 2021; 372: n71.

11.

Olesen

. Headache classification committee of the International Headache Society (IHS) the international classification of headache disorders, 3rd edition. Cephalalgia 2018; 38(1): 1–211.

12.

World Health Organization. ICD-9: basic tabulation list with alphabetic index. World Health Organization, https://apps.who.int/iris/handle/10665/39473 (1978, accessed 31 July 2022).

13.

World Health Organization. ICD-10: international statistical classification of diseases and related health problems, 2nd ed. World Health Organization, https://apps.who.int/iris/handle/10665/42980 (2004, accessed 31 July 2022).

14.

Wells

Shea

O’Connell

, et al. The Newcastle-Ottawa Scale (NOS) for assessing the quality of nonrandomised studies in meta-analyses, https://www.ohri.ca//programs/clinical_epidemiology/oxford.asp (2008, accessed 11 August 2022).

15.

Higgins

Thompson

Deeks

, et al. Measuring inconsistency in meta-analyses. Br Med J 2003; 327: 557–560.

16.

Galbraith

. A note on graphical presentation of estimated odds ratios from several clinical trials. Stat Med 1988; 7: 889–894.

17.

Begg

Mazumdar

. Operating characteristics of a rank correlation test for publication bias. Biometrics 1994; 50: 1088–1101.

18.

Egger

Davey Smith

Schneider

, et al. Bias in meta-analysis detected by a simple, graphical test. BMJ 1997; 315: 629–634.

19.

Duval

Tweedie

. A nonparametric “trim and fill” method of accounting for publication bias in meta-analysis. J Am Stat Assoc 2000; 95: 89–98.

20.

Pezzini

Grassi

Del Zotto

, et al. Migraine mediates the influence of C677T MTHFR genotypes on ischemic stroke risk with a stroke-subtype effect. Stroke 2007; 38: 3145–3151.

21.

Pezzini

Granella

Grassi

, et al. History of migraine and the risk of spontaneous cervical artery dissection. Cephalalgia 2005; 25: 575–580.

22.

Akova-öztürk

. Migräne-Risikofaktor für Sinusvenenthrombosen und Dissektionen? Aachen: Shaker Verlag, 2003.

23.

D'Anglejan-Chatillon

Ribeiro

Mas

, et al. Migraine - a risk factor for dissection of cervical arteries. Headache 1989; 29: 560–561.

24.

Artto

Metso

, et al. Migraine with aura is a risk factor for cervical artery dissection: a case-control study. Cerebrovasc Dis 2010; 30: 36–40.

25.

Zhou

Zheng

Gong

, et al. Vertebral artery hypoplasia and vertebral artery dissection: a hospital-based cohort study. Neurology 2015; 84: 818–824.

26.

Metso

Tatlisumak

Debette

, et al. Migraine in cervical artery dissection and ischemic stroke patients. Neurology 2012; 78: 1221–1228.

27.

Tzourio

Benslamia

Guillon

, et al. Migraine and the risk of cervical artery dissection: a case-control study. Neurology 2002; 59: 435–437.

28.

Thomas

Rivett

Attia

, et al. Risk factors and clinical presentation of cervical arterial dissection: preliminary results of a prospective case-control study. J Orthop Sports Phys Ther 2015; 45: 503–511.

29.

von Sarnowski

Schminke

Grittner

, et al. Cervical artery dissection in young adults in the stroke in young fabry patients (sifap1) study. Cerebrovasc Dis 2015; 39: 110–121.

30.

Garg

Bathla

Molian

, et al. Differential risk factors and outcomes of ischemic stroke due to cervical artery dissection in young adults. Cerebrovasc Dis 2020; 49: 509–515.

31.

de Giuli

Grassi

Lodigiani

, et al. Association between migraine and cervical artery dissection the Italian project on stroke in young adults. JAMA Neurol 2017; 74: 512–518.

32.

Metso

Salonen

, et al. Adult cervicocerebral artery dissection: a single-center study of 301 Finnish patients. Eur J Neurol 2009; 16: 656–661.

33.

Thomas

Rivett

Attia

, et al. Risk factors and clinical presentation of craniocervical arterial dissection: a prospective study. BMC Musculoskelet Disord 2012; 13: 164.

34.

von Sarnowski

Putaala

Grittner

, et al. Lifestyle risk factors for ischemic stroke and transient ischemic attack in young adults in the stroke in young fabry patients study. Stroke 2013; 44: 119–125.

35.

Etminan

Takkouche

Isorna

, et al. Risk of ischaemic stroke in people with migraine: systematic review and meta-analysis of observational studies. BMJ 2005; 330: 63.

36.

Spector

Kahn

Jones

, et al. Migraine headache and ischemic stroke risk: an updated meta-analysis. Am J Med 2010; 123: 612–624.

37.

Daghals

Sargurupremraj

Danning

, et al. Migraine, stroke, and cervical arterial dissection: shared genetics for a triad of brain disorders with vascular involvement. Neurol Genet 2022; 8: e653.

38.

Debette

Kamatani

Metso

, et al. Common variation in PHACTR1 is associated with susceptibility to cervical artery dissection. Nat Genet 2015; 47: 78–83.

39.

Loder

. Triptan therapy in migraine. N Engl J Med 2010; 363: 63–70.

40.

Hall

Brown

, et al. Triptans in migraine: the risks of stroke, cardiovascular disease, and death in practice. Neurology 2004; 62: 563–568.

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