How do various events in violent conflicts affect public opinion over time? This question lies at the heart of discussions about popular attitudes in contexts involving political violence, war, and reconciliation. Past research has significantly advanced our understanding of public reactions to key events in conflictual contexts, particularly violence by adversary groups (Godefroidt Reference Godefroidt2022). Violence, it finds, triggers meaningful emotional and attitudinal responses among the targeted population (see, for example, Berrebi and Klor Reference Berrebi and Klor2008; Echebarria-Echabe and Fernández-Guede Reference Echebarria-Echabe and Fernández-Guede2006; Huddy et al. Reference Huddy2005; Vasilopoulos et al. Reference Vasilopoulos2019). Nevertheless, this literature predominantly studies short or static time frames, exploring cross-sectional differences between individuals and contexts at frozen moments in time. We know far less about the temporal dynamics of these influences: Which events leave a longer mark on public opinion?; Does their impact vary in duration and erosion rate?; and What behavioral mechanisms do they imply?
In this article, we argue that the immediacy and longevity of public-opinion changes in ongoing conflicts vary by the type of event to which they react. We hypothesize that an adversary's violent actions, which pose a palpable threat to the in-group, trigger immediate but short-lived attitudinal reactions. This sudden and fleeting influence reflects not only instinctive emotional responses to the physical danger, but also cognitive desensitization to its broader informational signals. Conversely, non-violent events portraying salient new information about the conflict often have a lagged but longer-lasting attitudinal effect. Whereas the lack of immediate physical danger draws weaker emotional reactions in the short term, its new and complex information triggers slower but deeper belief-updating processes. We expect, therefore, that the second type of events, which are often overlooked in the literature, carry greater and longer-term implications for public opinion than violence.
We test these hypotheses on Jewish-Israeli public opinion regarding the Israeli–Palestinian conflict since the turn of the century. Using unique data from the Peace Index, a comprehensive monthly time series spanning two full decades (2001–20), we examine how aggregate attitudes react to real-world violence and non-violent events over time. We employ two complementary methods: first, an error-correction model that estimates average patterns of attitudinal shifts following pre-coded events; and, secondly, a structural breakpoint analysis that inductively identifies key moments of long-term attitudinal change. Like past research, we find that greater violence by the adversary promptly depresses aggregate support and hope for compromise among Jewish Israelis. However, public opinion quickly reverts to its previous levels. By contrast, failed negotiation summits and hawkish leadership changes by the Palestinians, both non-violent events signaling the latter's perceived intentions, exert a lagged but longer-lasting influence on Jewish-Israeli attitudes. Indeed, in the past two decades, the two largest structural attitudinal changes followed the non-violent victory of the militant movement Hamas in the 2006 Palestinian election and failed negotiation attempts in 2009. A close examination of these critical moments provides additional qualitative insight into their dynamics and the role of elite cues.
The article contributes to the larger debate about the temporal dynamics of public opinion, particularly in conflictual and violent contexts. Our findings demonstrate that changes in public attitudes vary in pace, duration, and size, depending on the type of threat and information to which citizens are exposed. While our analysis confirms that violence affects attitudes negatively, we demonstrate that such findings are incomplete without considering their temporal dimension. Moreover, focusing on immediate reactions and violence may miss the lagged but meaningful impact of non-violent developments, which can shape attitudes for months and years.
Whereas this insight is particularly relevant for active conflicts, it also applies to more sporadic incidents of terrorism and domestic violence with similarly fleeting attitudinal reactions (Arvanitidis, Economou, and Kollias Reference Arvanitidis, Economou and Kollias2016; Breton and Eady Reference Breton and Eady2022; Castanho Silva Reference Castanho Silva2018; Economou and Kollias Reference Economou and Kollias2019; Finseraas and Listhaug Reference Finseraas and Listhaug2013; Geys and Qari Reference Geys and Qari2017; Sharkey and Shen Reference Sharkey and Shen2021). It can further inform a broader range of questions about the short- and long-term influence of other threatening shocks, including economic crises, immigration waves, natural disasters, and other global and domestic events.
Finally, our findings are especially important to understand the types of factors and actions that advance or impede conflict resolution. Specifically, we demonstrate that non-violent actions and cues by local and international actors can significantly shift public opinion for lengthy periods, often unintendedly. Public signals about the conflict's future and each side's goals, therefore, should be planned carefully and strategically.
The article proceeds with a brief overview of existing explanations for attitudinal changes in conflictual settings and discusses their underexplored temporal dimension. We then suggest two dynamic logics that contrast immediate emotional reactions with slower belief-updating processes. After presenting the Israeli case and data, we test our expectations empirically and discuss broader implications and limitations.
Violence, Non-Violent Information, and the Missing Dynamic Perspective
An extensive literature studies the influence of real-world events on public attitudes in conflictual contexts. Of these factors, violent events receive the greatest attention (Godefroidt Reference Godefroidt2022). According to multiple studies, violence by an adversary group triggers negative emotions, such as anger, threat, and stress (Canetti-Nisim et al. Reference Canetti-Nisim2009; Halperin Reference Halperin2011; Huddy et al. Reference Huddy2005; Maoz and McCauley Reference Maoz and McCauley2005; Vasilopoulos et al. Reference Vasilopoulos2019), and increases ethnocentrism and intolerance (Echebarria-Echabe and Fernández-Guede Reference Echebarria-Echabe and Fernández-Guede2006; Kam and Kinder Reference Kam and Kinder2007; Peffley, Hutchison, and Shamir Reference Peffley, Hutchison and Shamir2015). These reactions affect political attitudes, amplifying: support for aggressive security policies (Brouard, Vasilopoulos, and Foucault Reference Brouard, Vasilopoulos and Foucault2018; Kupatadze and Zeitzoff Reference Kupatadze and Zeitzoff2021); preferences for hawkish and oppositionist politicians (Aytaç and Çarkoğlu Reference Aytaç and Çarkoğlu2021; Bali Reference Bali2007; Berrebi and Klor Reference Berrebi and Klor2008; Bonanno and Jost Reference Bonanno and Jost2006; Getmansky and Zeitzoff Reference Getmansky and Zeitzoff2014; Jaeger et al. Reference Jaeger2012; Kibris Reference Kibris2011); and reluctance to compromise with the out-group (Bayer, Klasen, and Adam Reference Bayer, Klasen and Adam2007; Canetti et al. Reference Canetti2017; Hirsch-Hoefler et al. Reference Hirsch-Hoefler2014).
Nevertheless, in some cases, violent events can instead increase popular support for peaceful agreements and moderate politicians (Arian, Shamir, and Ventura Reference Arian, Shamir and Ventura1992; Gould and Klor Reference Gould and Klor2010; Tellez Reference Tellez2019). Such conciliatory attitudes are more likely when the violence activates anxiety and weariness, concerns about future hostilities, and a greater desire to end the bloodshed (Beber, Roessler, and Scacco Reference Beber, Roessler and Scacco2014; Hazlett Reference Hazlett2020; Huddy et al. Reference Huddy2005).
While the influence of violence has been researched extensively, several behavioral studies find that public opinion also reacts to non-violent events conveying new information about the adversary's goals and the conflict. Such signals can include direct or indirect statements of out-group intentions (Hall et al. Reference Hall2018; Halperin et al. Reference Halperin2011; Leshem and Halperin Reference Leshem and Halperin2020), bilateral negotiation summits (Rosler, Cohen-Chen, and Halperin Reference Rosler, Cohen-Chen and Halperin2017), or positions taken by international actors (Shelef and Zeira Reference Shelef and Zeira2017). They are typically accepted more easily when reaffirming negative preconceptions of the conflict and out-group (Halperin and Bar-Tal Reference Halperin and Bar-Tal2011; Nyhan and Zeitzoff Reference Nyhan and Zeitzoff2018; Sheafer and Dvir-Gvirsman Reference Sheafer and Dvir-Gvirsman2010), though positive signals from the adversary can sometimes induce hope (Leshem Reference Leshem2019).
Nevertheless, most studies, whether focused on violent events or non-violent signals, share similar vagueness about their dynamic dimension. This ambiguity leaves several important questions under-studied: How long does the influence of different events endure in the public's mind?; How quickly do they take effect and at what pace do they erode?; and To what extent do they shape the long-term trajectory of public opinion? Many studies—particularly tests for causal mechanisms in controlled or quasi-controlled environments—examine attitudinal change immediately after specific events or stimuli. Others analyze their correlations with attitudes at a later but frozen point in time, be it days, weeks, or years after the event took place. These static lags between cause and effect are often selected by arbitrary data-collection limitations, rather than for theoretical or empirical reasons. Finally, even when the data include multiple periods, most time series tend to be short and sparse, and lack in-depth analyses of long-term temporal structures.Footnote 1
Immediate Threats and Long-Term Belief Updating
How, then, do violent and non-violent events influence public attitudes over time? All events can trigger emotional and cognitive reactions, yet we contend that violent and non-violent occurrences activate these mechanisms differently. Consequently, we expect that their temporal influence on public opinion—their immediacy, duration, and erosion rate—would vary too.
Events involving violence against the in-group pose an instant physical threat. Such palpable threats tend to trigger strong negative emotions and attitudes due to heightened mortality salience (Pyszczynski, Solomon, and Greenberg Reference Pyszczynski, Solomon and Greenberg2003) and concern for the in-group (Huddy et al. Reference Huddy2002; Wohl, Branscombe, and Reysen Reference Wohl, Branscombe and Reysen2010). Since such emotional reactions are linked to survival instincts, we expect them to appear immediately and strongly when the violence occurs but then wane quickly as the physical threat grows distant.
Violent events also convey information to the targeted population. Political violence is used to gain attention and signal the out-group's determination, capability, and willingness to impose painful costs to achieve its goals (Kydd and Walter Reference Kydd and Walter2006; Nussio, Böhmelt, and Bove Reference Nussio, Böhmelt and Bove2021). Such signals, however, are often unsuccessful (Abrahms Reference Abrahms2006; Gould and Klor Reference Gould and Klor2010). Violence is likelier to communicate new information in nascent or dormant conflicts with high uncertainty about the adversary's goals and behavior. Yet, once recurring, even in large intervals, violent actions become expected and familiar. Targeted group members, accordingly, become cognitively desensitized and less likely to change their attitudes (Liebes and Kampf Reference Liebes and Kampf2007; Nussio Reference Nussio2020).
Cognitive desensitization, nevertheless, does not undermine short-term emotional reactions to violent threats (Nussio Reference Nussio2020). Hence, in contexts where the adversary's goals and violence are familiar, we expect that violent events cause only an immediate but fleeting influence on attitudes. As discussed earlier, the literature has mixed expectations about the direction of this influence. Accordingly, we propose two competing hypotheses:
Hypothesis 1a (H1a): Greater violence will increase hawkish attitudes about the conflict immediately but only for a brief period.
Hypothesis 1b (H1b): Greater violence will decrease hawkish attitudes about the conflict immediately but only for a brief period.
The second type of events signal new information about the adversary and the conflict without using violence. This broad category can take various idiosyncratic forms, including elite actions, international incidents, or domestic political events. Nevertheless, several common features are required, as such events must: portray new information about the adversary's goals or the conflict's future; be publicly and broadly visible; and lack a palpable physical threat.Footnote 2 Consider, for example, public negotiation meetings, which send visible signals about the adversary's demands and willingness to compromise (or lack thereof). A similar cue appears when the out-group selects new leaders with more moderate or extreme positions about the conflict. Actions by the international community can also send salient indications about the conflict's future.
Contrary to violence, the lack of physical threat in non-violent events should weaken immediate emotional reactions and increase the role of cognition (Gordon and Arian Reference Gordon and Arian2001). Moreover, such signals are typically more complex. Whereas violence sends a simple message due to its embedded danger—the adversary physically threatens the in-group—non-violent events carry greater uncertainty. Deciphering such new and complex information requires additional top-down cues and public narratives that take longer to process (Berinsky Reference Berinsky2009; Zaller Reference Zaller1992). Hence, non-violent events signaling new information about the adversary should influence popular attitudes slower. However, once they do, this cognitive channel can update beliefs more fundamentally and for lengthier periods. Therefore, we suggest the following hypothesis:
Hypothesis 2 (H2): Non-violent events carrying salient negative (positive) new information about the adversary will increase (decrease) hawkish attitudes about the conflict more slowly but for longer periods than violence.
One caveat is in order. In extreme cases, the emotional influence of violence can create lasting traumas that sustain long after the danger passes. This often occurs in individuals that experience violence directly and develop post-traumatic stress disorder (Bonanno and Jost Reference Bonanno and Jost2006; Hirsch-Hoefler et al. Reference Hirsch-Hoefler2014), yet they are usually too few to shift aggregate public opinion. However, outstanding atrocities, such as indiscriminate mass violence or forced population transfers, can form lasting collective victimhood narratives that are passed down through generations (Balcells Reference Balcells2012; Lupu and Peisakhin Reference Lupu and Peisakhin2017; Rozenas, Schutte, and Zhukov Reference Rozenas, Schutte and Zhukov2017). Our argument disregards such extreme cases given their rarity, but researchers studying violence of this scale should adjust their analyses accordingly.
In what follows, we test our hypotheses empirically using dynamic analyses of hundreds of monthly public opinion surveys conducted in Israel regularly over two decades. The data's high frequency and longevity allow us to analyze how aggregate attitudes on the conflict respond to various violent and non-violent events, how quickly they react, and how long the change endures. Before elaborating on our methodological approach, we first discuss our case study and data.
The Israeli Case
The Israeli–Palestinian conflict has long been a central case study for political behavior in conflictual contexts. The conflict has been a constitutive issue in Israeli society and politics (Arian and Shamir Reference Arian and Shamir2008; Shamir and Arian Reference Shamir and Arian1999; Yakter and Tessler Reference Yakter and Tessler2022), yet despite its enduring presence, it has been quite dynamic. In the past decades, the Israeli public faced differing degrees of violence, including two large-scale violent campaigns (intifadas), ebbs and flows of small-scale terrorist attacks and rocket shelling, and extended calmer periods.Footnote 3 The nature of violence itself varies too, shifting periodically between local stone throwing, lone-wolf attacks, large-scale suicide and car bombings, and rocket shelling. The conflict has also provided multiple non-violent opportunities to assess the other side's intentions. The past decades included several rounds of peace negotiations, some prolonged with meaningful advancements, particularly in the 1990s and briefly in the mid-2000s, and others shorter and futile. Both sides also made leadership changes over the years, signaling alternating popular support for more combative or moderate visions of the conflict.
The temporal variation in violent and non-violent events deem Israel particularly fitting to test our argument. They also mark the boundaries of our analysis, a point discussed further in the article's conclusion. Most significantly, the conflict's rich temporal dynamics are testable due to its protracted nature. As such, our broader inferences should be considered carefully where hostilities are experienced as a single shock with long-term traumatic effects and/or the adversary is relatively unfamiliar. Nevertheless, as Peffley, Hutchison, and Shamir (2015, 819) observe, Israel's experience with violence is “distinctive but not unique” and comparable with dozens of other countries. As more societies endure recurrent political violence, so do Israeli patterns become more relevant and generalizable.
Public Attitudes about the Conflict: The Peace Index Data
Our primary outcome of interest is Israeli public attitudes toward the conflict. To examine these attitudes over time, we pooled hundreds of public opinion surveys from the Peace Index, a survey project established in the 1990s at Tel Aviv University. The Peace Index has regularly conducted monthly representative surveys with a small set of recurring questions about the peace process, alongside interchanging questions on current events. These data, therefore, offer a unique opportunity to examine national attitudes on the conflict using identical questions in short and regular intervals over two full decades.
We analyze two dependent variables based on a pair of recurrent questions asked regularly starting in July 2001. The first gauges ideological support for negotiations as follows: “What is your position on conducting peace negotiations between Israel and the Palestinian Authority?” The second measures pragmatic hope for an agreement as such: “Do you believe or not believe that negotiations between Israel and the Palestinian Authority will lead in the coming years to peace between Israel and the Palestinians?” Both offer a four-point answer scale from “Strongly in favor/believe” to “Strongly opposed/do not believe at all.”
Both questions tap into hawkish/dovish attitudes about the conflict, its future, and the adversary. Accordingly, we expect both indicators to react similarly to the conflict's events. Nevertheless, we analyze them separately because their core sentiments—ideological preference and pragmatic expectation—are interrelated but not analytically identical (Leshem and Halperin Reference Leshem and Halperin2020). While their similarities and differences are outside the scope of this article, identifying potential variations and parallels can add further depth to our analysis and directions for future research.
Whereas each monthly survey draws a new respondent sample, their representative design produces a reliable time series of aggregate public attitudes. Accordingly, our two dependent variables measure the monthly aggregate net support for each statement, that is, the total share of negative answers subtracted from the share of positive answers every month. Since Arab citizens have been included inconsistently throughout the series, we aggregate only answers from Israel's Jewish majority. Moreover, we expect Arab citizens, many of whom identify as ethnic Palestinians, to display different attitudinal patterns regarding the conflict. Hence, the reactions of minority ethnic groups in ethnonational conflicts merit a separate theoretical and empirical framework outside the scope of this article.
Both variables comprise 227 months from July 2001 to May 2020. Of these months, twenty-five have missing observations. Section 2 in the Online Supplementary Material (OSM) demonstrates that the missing observations are spaced far apart and uncorrelated with the conflict's violence and non-violent events. Additionally, both indicators display strong serial autocorrelation. Hence, we impute the missing observations using a simple linear interpolation. Section 2 in the OSM offers additional discussion and robustness tests for this choice.
Figure 1 plots both time series. The data show that aggregate net support for negotiations has remained positive throughout the past twenty years, notwithstanding occasional ebbs and flows. Aggregate net hope of their prospects is consistently lower than, though noticeably correlated with, the former. We examine the dynamic nature of these trends using two complementary methods. First, we estimate a general error-correction model (GECM) with prespecified explanatory variables to find average reactive patterns throughout the entire period. Secondly, we employ a structural breakpoint analysis to inductively identify critical junctures of long-term attitudinal change and then qualitatively investigate nearby events and implied mechanisms. Together, the two methods establish a robust dual test for our hypotheses. We discuss each set of findings in turn.
Figure 1. Net support for negotiations and net hope about peace in practice, 7/2001–5/2020.
Average Patterns of Attitudinal Change
Independent Variables
We begin by estimating attitudinal changes by several independent variables measuring monthly violence levels and non-violent signals. Two variables gauge the monthly levels of Palestinian violence experienced by Israelis. The first counts the monthly number of Israeli casualties by Palestinian actions.Footnote 4 Given the country's mandatory military service and high sensitivity to combat deaths (Levy Reference Levy2012), we count both civilian and security forces fatalities. The second variable measures the monthly number of rockets shot at Israel from the Gaza strip.Footnote 5 Palestinian factions began using rockets in the early 2000s and quickly increased their volume and range, now reaching the most populous areas in central Israel. Whereas these rockets are less deadly than other forms of violence, they are aimed indiscriminately at civilians and cause meaningful psychological, social, and political effects (Besser and Neria Reference Besser and Neria2009; Getmansky and Zeitzoff Reference Getmansky and Zeitzoff2014; Zeitzoff Reference Zeitzoff2014). Since casualties and rockets have unevenly high peaks and decreasing marginal influence, we take the natural logarithm of both.Footnote 6
Next, we construct two variables to measure non-violent events signaling Palestinian intentions. Coding such events ex ante is not trivial. Since they can take multiple idiosyncratic forms, an open coding scheme may introduce coder bias in favor of high-impact events, while overlooking comparable incidents with low influence. Thus, we focus conservatively on two event types that can be coded systematically.Footnote 7 The first variable is a dummy indicating months with public Israeli–Palestinian negotiation meetings. Public negotiation summits send salient signals about the out-group's demands, willingness to compromise, and distance from the in-group's positions. Our data include five negotiation meetings between 2001 and 2020 that were publicly known in real time. Such meetings can send either a negative or a positive signal, depending on their conclusions. However, due to their futility throughout our sample, we code all these meetings as negative signals.
The second variable gauges Palestinian hawkish leadership selection using a categorical score that indicates months signaling either a militant (1) or moderate (−1) leadership change. The popular choice of hawkish or moderate leaders sends a visible signal about greater public support for their visions of the conflict. Our sample includes four such moments. In January 2005, a positive signal was sent when the relatively moderate Mahmoud Abbas was elected president after Yassir Arafat's death.Footnote 8 The three negative events signaled popular support for Hamas, a militant Islamist movement that has continuously engaged in violence against Israel: in March 2006, Hamas formed the Palestinian government for the first time after winning a majority of seats in the legislative election; in March 2007, it headed a new unity government with the more moderate Fatah party; and in July 2007, after the unity agreement collapsed, it forcibly took control over the Gaza Strip and formed a parallel government to Fatah's West Bank administration.Footnote 9
We also include three control variables. First, we calculate the share of Israeli cabinet ministers from right-wing parties to control for similar dampening signals about the preferences of fellow Israelis.Footnote 10 Secondly, we use the real average monthly wage of Israeli hired workers (constant 2011 prices) to control for the state of the economy, which may influence the public mood regardless of the conflict.Footnote 11 Third, we include a monthly time trend (that is, a monthly counter) to account for a possible monotonic decline in support or hope for peace irrespective of specific events. Section 1 in the OSM presents descriptive plots of all variables.
Model Setup
To examine the dynamic relationship between the two attitudinal variables and our independent variables, we estimate a GECM using an ordinary least squares (OLS) regression (De Boef and Keele Reference De Boef and Keele2008). The GECM regresses changes in the dependent variable on its own lagged value and on both the first differences and the lagged values of the independent variables. Formally, the GECM is specified as follows:
$$\Delta y_t = \alpha _0 + \alpha _1y_{t-1} + \beta _0^{\rm ^{\prime}} \Delta X_t + \beta _1^{\rm ^{\prime}} X_{t-1} + \varepsilon _t,\eqno \;$$ where Δy t is the change in the dependent variable, α 1 estimates the influence of its levels one period earlier (also known as the error-correction term), 
$\beta _0^{\rm ^{\prime}} $ estimates the immediate effects of a one-unit change in independent variables X t, and 
$\beta _1^{\rm ^{\prime}} $ estimates the lagged effect of the latter's levels in the previous period. The inclusion of both first differences and lagged values separates each independent variable's immediate and delayed effects on the outcome. The model's error-correction term (α 1) reflects the monthly rate at which the outcome adjusts back to its former levels after the explanatory variables changed. Hence, it tells us how quickly their influences erode.
To avoid bias, the GECM requires that all variables have the same order of integration (Grant and Lebo Reference Grant and Lebo2016; Keele, Linn, and Webb Reference Keele, Linn and Webb2016). Multiple unit root tests, specified in Section 4 in the OSM, indicate that all our variables are stationary except the share of Israeli right-wing cabinet seats. This variable, therefore, is modeled only at first difference.
We select the GECM's proper number of lags using a general-to-specific approach, detailed in Section 5 in the OSM. In short, we iterated our models with different combinations of lag lengths for each variable, picking the number of lags that optimized model fit and coefficient t-tests scores. The procedure favored a single monthly lag for logged rockets, logged casualties, and average wage, and two-monthly lags for negotiation meetings and Palestinian leadership changes, foreshadowing a temporally intricate effect, as we shall see.Footnote 12
Finally, we tested for serial autocorrelation in our models using Ljung–Box and Breusch–Godfrey tests. In both series, dynamic completeness is achieved after adding the first difference of the lagged dependent variable (Δy t−1). Additional Ljung–Box tests reject concerns of seasonality in the data. Section 6 in the OSM details these tests.
GECM Findings
Table 1 presents the GECM estimations. For ease of interpretation, both net attitudes are measured on a scale of 1–100, rather than percentages. The first-difference coefficients indicate that greater violence leads to an instant decline in both net support and net hope for peace. On average, a one-standard-deviation increase in the logged number of rockets immediately lowers the aggregate net support for negotiations by 1.57 points and net hope in their prospects by 1.15 points. Similarly, a one-standard-deviation increase in logged casualties instantly decreases net support for negotiations by an average of 1.92 points and net hope by 1.72 points. These results corroborate the hypothesis that greater violence immediately dampens public attitudes regarding resolution (H1a) and rejects a positive relationship (H1b). Conversely, we do not see sudden attitudinal changes following negotiation meetings or Palestinian leadership changes, consistent with their expected lagged effect (H2).
Table 1. Aggregate attitudinal changes
Notes: The dependent variables use a 1–100 scale. Standard errors in parentheses. †p < 0.1; *p < 0.05; **p < 0.01; ***p < 0.001. §Indeterminate statistical significance (middle category) of long-term relationship at the 95 per cent level using the bounds test from Webb, Linn, and Lebo (Reference Webb, Linn and Lebo2020) assuming five variables and 150 observations. The LRM standard errors are calculated with the delta method. Cumulative sum (CUSUM) tests verify parameter stability throughout both series.
We examine the model's longer temporal dynamics in two steps. First, we calculate each explanatory variable's long-run multiplier (LRM), presented at the bottom of Table 1. Calculated as LRMx = −(β 1/α 1), these scores reflect the total cumulative influence of each independent variable across all future months. We estimate the LRMs' confidence levels using the bounds test proposed by Webb, Linn, and Lebo (Reference Webb, Linn and Lebo2020). The test has three possible outcomes: no long-term relationship (a t-statistic below the lower bound); a statistically indeterminate long-term relationship (a t-statistic in between the bounds); and a statistically significant long-term relationship (a t-statistic above the upper bound). Most LRMs in our model fit the middle category, indicating ambiguous statistical confidence. Rockets, however, have a strictly insignificant long-run effect.Footnote 13
Secondly, we compute the temporal distribution of these cumulative effects over time. This calculation is based on each variable's immediate effect at time t (β 0), follow-up effect at t + 1 (β 1) and t + 2 where relevant, and monthly erosion rate thereafter (α 1). Figure 2 plots the monthly distribution of each variable's long-term influence after a one-off one-standard-deviation increase. Negotiations and hawkish leadership change, which are binary/categorical, are assumed to increase by one unit.
Figure 2. Lag distribution after a one-standard-deviation increase in each independent variable (dummy/categorical variables increase by 1).
The resulting patterns tell a temporally intricate story. In both models, the negative influence of rocket shelling lapses after a single month. An increase in casualties has a similarly fleeting effect on the aggregate hope for peace, though its influence on the willingness to negotiate is slightly less forgiving: a one-standard-deviation increase creates an immediate negative decline of 1.92 points, but its cumulative effect reaches 6.23 points, on average, over the next four to five months. More casualties, therefore, do not deepen pessimism about the prospects of peace beyond a single month, but they do have a slightly larger and longer dampening influence on support for diplomacy. While mostly similar, this nuance is intriguing enough to justify additional research. Nevertheless, the broader pattern supports H1a: greater violence levels undermine support and hope for compromise immediately but also rather briefly.
Non-violent political events exhibit the opposite dynamic. Both negotiation meetings and hawkish leadership changes cause a lagged but longer-term demoralization in public attitudes, barely moving at first but then plummeting two months later and eroding slowly thereafter. Curiously, hawkish leadership changes create a positive immediate effect, perhaps reflecting an initial hope for pragmatic moderation under the pressures of leadership. Nevertheless, this effect is statistically insignificant and turns negative one month later. While the LRM bounds tests are statistically indeterminate regarding the full extent of these long-run influences, the GECM indicates that the largest dip, taking place at t + 2, is statistically significant for both negotiations and leadership changes. These results, therefore, support H2, indicating that informational signals have a lagged but prolonged influence on aggregate public attitudes regarding resolution.
An Inductive Analysis of Influential Events
The GECM estimation is instructive but has several limitations. First, it models average attitudinal changes after events that can be coded systematically, yet such incidents can take various idiosyncratic forms that are hard to operationalize ex ante. This is particularly true for singular moments, such as deeply traumatic violent acts or other unique events reshaping prior conceptions. Secondly, the statistical indetermination of the LRM bounds tests muddies our full confidence in the long-term influence of non-violent signals. Finally, the average patterns provide little information about the real-world dynamics accompanying moments of prolonged attitudinal change.
To address these issues, we employ an inductive structural breakpoint analysis of the two series. Rather than prespecified events, structural breakpoint analyses detect moments of significant change based on the underlying structure of the data. Once such points are identified statistically, we can qualitatively examine real-world events that occurred at these times and assess their fit with our hypotheses (Caporale and Grier Reference Caporale and Grier2005; Wawro and Katznelson Reference Wawro and Katznelson2014). Theoretically, we expect that long-term breaks in the two series will follow salient non-violent events signaling Palestinian intentions and the conflict's future, rather than violent escalations. Moreover, if our hypotheses are too narrow, this approach can discover other influential event types that we may have missed.
We estimate structural breakpoints in our data using Bai and Perron's method, which allows for multiple breaks in each series (Bai and Perron Reference Bai and Perron1998; Bai and Perron Reference Bai and Perron2003). A Zivot–Andrews unit root test confirms that both attitudinal series are breakpoint stationary. We use a standard trimming parameter value of 0.15 and determine the number and position of the estimated breakpoints with a sequential l + 1 breaks versus l test.Footnote 14 Since both series show signs of trend stationarity, we include a temporal trend term in the estimation.
Figure 3 plots the estimated breakpoints in aggregate net support and hope for compromise. In each series, the dashed vertical lines mark identified breakpoints, while the fitted lines display the average trend in each subperiod. The aggregate net support for negotiations, presented in the top panel, has three estimated breakpoints: January 2006 (A), April 2009 (B), and October 2016 (C). The aggregate net hope for peace, plotted in the bottom panel, has two estimated breakpoints: April 2006 (D) and September 2013 (E).
Figure 3. Structural breakpoints (dashed vertical lines) in aggregate net support for negotiations (top panel) and net hope for peace (bottom panel).
Table 2 summarizes the descriptive characteristics of these breakpoints. The first two columns indicate whether each structural breakpoint displays changes in absolute levels and/or a long-term trend and their direction.Footnote 15 These shifts show both the similarities and differences between the two series. Both ideological support for negotiations and hope about their prospects grew similarly during the early 2000s and experienced a parallel sharp drop in early 2006 (Points A and D) that lasted several years.Footnote 16 The aggregate net support for negotiations, though not net hope, temporarily bounced back in early 2009 (Point B) before gradually eroding again. Practical hope for peace, conversely, never rebounded after 2006. The last breakpoints in both series—September 2013 (Point E) and October 2016 (Point C)—exhibit smaller changes in levels without shifting the long-term trend.
Table 2. Structural breakpoint characteristics
Note: The direction of change in levels and trends is supported by a series of interrupted time-series models (see OSM Section 7.1). Violence levels are considered vis-à-vis sample and annual averages (see OSM Section 7.2).
Which factors explain these breaks? The third column in Table 2 summarizes the relative rocket and casualty levels at each point compared to their sample averages. Corroborating our hypotheses and earlier findings, none of the long-term breaks occurred in particularly violent moments. By contrast, as the fourth column indicates, all moments can be linked with non-violent events that sent salient signals about Palestinian preferences and/or the conflict's future. Moreover, most involve leadership changes or failed negotiations. To gain better insight into their influence, we turn to examine each moment in greater detail. We pay particular attention to the first three breakpoints, which exhibit the largest structural changes in both attitudinal levels and trends.
January–April 2006: Hamas's Electoral Victory
The first notable breakpoint in both series occurred in January–April 2006 (Points A and D). The early months of 2006 featured two political developments: the Palestinian legislative elections and subsequent government formation (January and April); and the Israeli general election (March). Of the two, the Israeli election seems less consequential. The incumbent party, Kadima, won the election handily. According to the post-election Peace Index survey, most respondents supported the winning coalition and split along expected partisan and ideological lines. The Israeli election, therefore, reinforced the political status quo.
The Palestinian election, by contrast, seems like a watershed moment. The Palestinian Legislative Council election was held for the first time in a decade after the Fatah party's long single-party reign. Yet, defying earlier expectations, the more extremist Hamas won most seats. In reality, Hamas's success reflected public frustration with Fatah, infighting among their opponents, and advantageous electoral rules, rather than popular support for its militant agenda (Shamir and Shikaki Reference Shamir and Shikaki2010). However, to Israeli eyes, the victory signaled Palestinian endorsement of violent extremism. In the January 2006 Peace Index survey, 60 per cent of Jewish respondents stated that Hamas's victory posed an existential threat to Israel and 74 per cent predicted little to no chance that Hamas will eventually recognize Israel's right to exist. Moreover, 55 per cent of Jewish respondents opposed direct negotiations with a Hamas-led government and 87 per cent estimated that there is little to no chance of reaching a peace agreement with it.
The negative signal about Hamas's victory developed further in the following weeks with additional elite cues, fitting the lagged structural break in aggregate hope in April 2006. Following the election, the Middle East Quartet—the United States, the European Union, the United Nations, and Russia—demanded publicly that any Hamas-led government recognize Israel, accept previous bilateral agreements, and commit to non-violence. Hamas, however, blatantly rejected these conditions, triggering severe international and Israeli economic sanctions once the new government was formed. The Israeli public took notice: the Peace Index survey conducted in late March 2006, two months after the election, showed an increase in the share of Jewish respondents doubting that Hamas will moderate its violence (79 per cent compared to 50 per cent in January) and objecting to direct negotiations with the movement (57 per cent compared to 54 per cent in January). Hence, Hamas's public refusal to disavow violence and recognize Israel after its victory, combined with aggressive international and Israeli delegitimization campaigns, explicated the notion of Palestinian preference for violent extremism over compromise. The result was a prolonged drop in aggregate Jewish-Israeli support and hope for compromise.
Early 2009: US-Led Diplomatic Momentum and Failure
Our analysis finds that net support for negotiations, though not practical hopes for peace, bounced back around April 2009 (Point B) before declining again in the following year. The main occurrence in early 2009 signaled a new momentum in the peace process following political shifts in the United States and Israel. In January 2009, US President Barack Obama took office, with high expectations for a new diplomatic approach after the hawkish Bush years. Obama quickly appointed George Mitchell, known for his involvement in Northern Ireland's Good Friday Agreement, as his special envoy for restarting Israeli–Palestinian negotiations. Meanwhile, in Israel, a new government headed by Benjamin Netanyahu entered office in March and was immediately pressured on this issue by the United States. In March–April 2009, Israel hosted formal visits by Mitchell and Secretary of State Hillary Clinton, during which she publicly expressed support for territorial compromise and objection to Israel's settlement policy. Additionally, an Obama–Netanyahu meeting was set for May with this agenda in mind. In the March 2009 Peace Index survey, 62 per cent of Jewish respondents estimated that the Israeli government would strive to maintain a good relationship with the United States regarding peace negotiations and would face severe pressure from Obama if not. Hence, the flurry of preparations in the spring of 2009 sent a visible signal that the US administration was determined to revive the peace process and that agreeing to negotiations was in Israel's best interest. The lack of a similar rise in hope for peace may indicate that many waited for substantial signs that the Palestinians were similarly committed.
Subsequent developments over the following months help explain the slow but renewed decline in support for negotiations. The momentum continued during the summer, with Obama's dovish Cairo Speech and Netanyahu's acceptance of the two-state solution in his Bar-Ilan University address. Furthermore, in November 2009, Israel announced a ten-month settlement construction freeze following intense US pressure. By its conclusion in September 2010, Israeli and Palestinian representatives were set to meet for direct peace talks.
Yet, the first cracks appeared early and gradually expanded. Despite Netanyahu's endorsement of the two-state solution, he developed a visibly strained relationship with Obama and repeatedly demanded strict preconditions for an agreement, particularly formal Palestinian recognition of Israel as the state of the Jews. During the September 2010 talks, Israel's leadership continued to raise this demand publicly and refused to extend the settlement freeze without it. Most Israelis internalized this cue: in the Peace Index survey from October 2010, 75 per cent of Jewish respondents justified Netanyahu's demand for Palestinian recognition and 81 per cent agreed that the Palestinians do not accept Israel's existence and would destroy it if they could. The negotiations quickly imploded, leading the frustrated US administration to shift focus to other foreign policy areas. Both the initial momentum in early 2009 and its subsequent failure are mirrored well in the rise and fall of aggregate support for negotiations, corroborating our earlier findings of the lagged but long-term influence of failed diplomacy.Footnote 17
September 2013: More Futile Negotiations
The last two breakpoints exhibit smaller but noticeable breaks in attitudinal levels without changing their previous temporal trends. Nevertheless, they too align with discernible non-violent signals about the adversary and conflict's future. The first (Point E) shows a decline in practical hope for peace in September 2013, two months after another round of failed negotiations initiated by US Secretary of State John Kerry. Unlike the positive momentum in 2009, Kerry's initiative never gained steam and ended with a whimper. While the Jewish-Israeli public was initially skeptical, it nevertheless grew more doubtful after their failure. In the Peace Index survey from June 2013, before the negotiations started, 71.3 per cent estimated that Kerry's initiative had low or very low success odds. After the meetings, this share grew to 79.4 per cent in July and 81.2 per cent in September. Hence, even a swift, low-key diplomatic failure caused an additional long-term decline in aggregate hope for peace. Fitting our GECM findings, this change became more pronounced a month or two after the direct meetings, as the extent of the failure was properly processed.
October 2016: Trump's Election
The last structural breakpoint (Point C) identifies rising support for negotiations after October 2016. The most notable event at this moment was US President Donald Trump's electoral victory in early November.Footnote 18 In the Peace Index survey conducted right after the election, 48.5 per cent of Jewish Israelis estimated that Trump favors Israel over the Palestinians and 61.8 per cent assumed he would not oppose and would even support settlement construction. By contrast, only 22.2 per cent stated that Obama was friendly to Israel throughout his term. Hence, Trump's victory signaled unconditional US support for Israeli demands, leading to a better bargaining position than the Palestinians. This cue helps explain the structural bounce in willingness to negotiate even as practical hopes for peace remained low. This signal does not involve Palestinian intentions, yet it too illustrates the importance of new non-violent information about the conflict's balance of power.
Conclusion
Public opinion is a key aspect of violent conflicts, establishing bottom-up pressures that can escalate or moderate the conflict's future path. Accordingly, a large literature explores various factors influencing public attitudes in conflictual contexts, with a particular focus on violent incidents. Nevertheless, past findings mostly highlight short-term or static attitudinal reactions, providing incomplete accounts of their full temporal dynamics and other types of influences.
Using two decades of monthly surveys from Israel, we argue that popular reactions to real-world events have a meaningful, yet largely under-studied, temporal dimension. Our findings show that Jewish-Israeli support and hope for compromise decreases immediately after violent escalations, but this influence lapses quickly and leaves little to no mark on the long-term trajectory of public opinion. Conversely, non-violent events carrying visible informational signals about the adversary and the conflict—particularly failed negotiations and Palestinian leadership changes—have a lagged but larger and longer effect on public attitudes. This conclusion is supported by both average patterns found with a GECM and an inductive structural breakpoint analysis matched with real-world events.
These divergent temporal patterns are consistent with our suggested theoretical logic. The sudden but fleeting effect of violence implies not only an instinctive emotional reaction to a palpable danger, rising and falling with its physical threat, but also cognitive desensitization. Meanwhile, the lagged but longer-lasting reactions to non-violent signals suggest deeper belief updating following gradual cognitive processing of new information and top-down cues. While we do not test these mechanisms directly, our aggregate findings open new avenues for micro-behavioral research on their operation, different temporal implications, and interrelations. Moreover, given the literature's focus on violence, more theoretical and empirical work is needed on different types of informational signals in conflictual environments. Our findings, for example, imply that unexpected information (for example, Hamas's surprising electoral victory) may have a longer attitudinal influence than expected events.
This point is particularly important for real-world conflict resolution efforts. Our findings show that public attempts to resolve conflicts by international and domestic actors can be a double-edged sword if unsuccessful. In Israel, futile negotiation initiatives, especially when pushed by outside actors, not only failed to advance peace, but also left an enduring negative mark on Jewish-Israeli attitudes. Similarly, international and domestic framings of the out-group's political choices, such as the negative campaign against Hamas's looming government, can have long-lasting adverse implications for public attitudes about resolution. Even indirect cues, such as unconditional one-sided support by international actors, can move public opinion in meaningful ways (see Shelef and Zeira Reference Shelef and Zeira2017). Insofar as popular attitudes matter for peace, actions and cues by global and local elites must be taken carefully and with proper consideration of their potential long-term repercussions.
As noted earlier, while our focus on the Israeli–Palestinian conflict offers important insights, it also raises questions about generalizability. Three issues stand out, marking both the promise and limits of our conclusions, and paths for further comparative research. First, the longevity, intensity, and embeddedness of the Israeli–Palestinian conflict raise the concern that Israelis have become uniquely desensitized to violence (see Nussio Reference Nussio2020). This worry, however, is inconsistent with a large body of evidence showing that the conflict's violence constantly triggers emotional, attitudinal, and behavioral reactions in Israel (for example, Berrebi and Klor Reference Berrebi and Klor2008; Besser and Neria Reference Besser and Neria2009; Getmansky and Zeitzoff Reference Getmansky and Zeitzoff2014; Gould and Klor Reference Gould and Klor2010; Hirsch-Hoefler et al. Reference Hirsch-Hoefler2014). Moreover, multiple findings from other Western countries show that sparser terrorist and civilian attacks have likewise caused only short-lived attitudinal shifts regarding security policies, social trust, and out-group resentment (Arvanitidis, Economou, and Kollias Reference Arvanitidis, Economou and Kollias2016; Breton and Eady Reference Breton and Eady2022; Castanho Silva Reference Castanho Silva2018; Economou and Kollias Reference Economou and Kollias2019; Finseraas and Listhaug Reference Finseraas and Listhaug2013; Geys and Qari Reference Geys and Qari2017; Sharkey and Shen Reference Sharkey and Shen2021). Thus, we expect similar temporal patterns elsewhere, including in shorter and less salient violent contexts, though more comparative dynamic analyses are needed.
Secondly, the period that we analyze had few positive diplomatic breakthroughs. Our data, accordingly, do not test how aggregate public attitudes react to positive negotiation advancements, which often also involve temporary setbacks and violence. Descriptive data from the 1990s, the heyday of the Israeli–Palestinian peace process, fail to show notable spikes in Israeli attitudes during constructive diplomatic developments (Hermann and Yuchtman-Yaar Reference Hermann and Yuchtman-Yaar2002). This pattern fits the expectation that negative signals are more influential than positive ones. Nevertheless, recent experimental research finds that optimistic information about the adversary can increase support for compromise under certain conditions (Halperin et al. Reference Halperin2011; Leshem and Halperin Reference Leshem and Halperin2020). Hence, we need additional dynamic analyses of attitudinal changes in periods and regions experiencing real progress toward resolution.
Finally, our analysis of Jewish-Israeli popular reactions focuses on the stronger group in an asymmetrical conflict. However, these processes may manifest differently among minority or weaker groups in uneven settings. Jaeger et al. (Reference Jaeger2012) find not only similar short-lived Palestinian reactions to targeted Israeli violence, but also a greater sensitivity to collateral violence, which is endured more regularly in the territories. Accordingly, more direct comparisons of dynamic reactions across asymmetrical power hierarchies are required. Our findings, we hope, help facilitate such future endeavors.
Supplementary Material
Online appendices are available at: https://doi.org/10.1017/S0007123422000400
Data Availability Statement
Replication data for this article can be found in Harvard Dataverse at: https://doi.org/10.7910/DVN/FKKJTQ.
Acknowledgments
We thank Daniel Arnon, Daphna Canetti, Avishay Ben Sasson-Gordis, Lior Lehrs, Carmela Lutmer, Quinn Mecham, Anil Menon, Nimrod Rosler, Tolga Sinmazdemir, Matthew Ward, and the BJPS editors and reviewers for their helpful comments and suggestions. We are also grateful to Mohammad Saad for excellent research assistance. Earlier versions of this paper were presented at the annual meetings of the American Political Science Association (in 2020), the Midwest Political Science Association (in 2021), the European Political Science Association (in 2021), the International Society for Political Psychology (in 2021), and the Israeli Association for International Studies (in 2021).
Financial Support
This research was supported by the Israel Science Foundation (Grant No. 2976/21).
Competing Interests
None.
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