From Disruption to Integration: Cryptocurrency Prices, Financial Fluctuations, and Macroeconomy

Q: What drives cryptocurrency price shocks — sentiment, technology, or regulation?

Sentiment and technology — not regulation or monetary policy. Chen (2025) classifies 67 major crypto-market events 2014–2023 into six categories and finds only sentiment (coefficient 1.36, t = 3.15) and technology (coefficient 1.02, t = 2.06) significantly explain the identified structural crypto shocks. Regulatory, monetary, infrastructure, and network-effect shocks are statistically insignificant. The narrative identification follows Romer and Romer (2004) . Sentiment dominance validates Baker and Wurgler (2007) , while the significant technology coefficient shows crypto is not pure speculation. This partially contradicts regulation-focused studies including Borri and Shakhnov (2020) and Chokor and Alfieri (2021) .

Q: How does cryptocurrency transmit to the real economy?

Cryptocurrency shocks now transmit through a dual-channel: sentiment drives financial-market integration and technology drives real-economy effects. Chen (2025) documents that a one-standard-deviation positive Bitcoin price shock produces a sustained 1.2% rise in the S&P 500, a 2% rise in the CRB commodity index, a delayed 0.15% rise in industrial production, a persistent 0.02% decline in unemployment, and a 0.15% rise in the PCE price index over a 30-month horizon. The real-economy effects are quantitatively modest but theoretically grounded in investment-channel mechanics from Jermann and Quadrini (2012) and uncertainty-channel mechanics from Bloom (2009) .

Q: Why use Bayesian SVAR with Pandemic Priors for this question?

Use Pandemic Priors. Cascaldi-Garcia (2022) proposes extending the Minnesota prior with time dummies for the pandemic period, controlled by a hyperparameter φ. As φ → 0 pandemic observations are treated as exceptional; as φ → ∞ the setup reverts to conventional Minnesota priors. Chen (2025) selects φ = 0.1 by marginal-likelihood maximization over a grid from 0.001 to 500, using the dummy-observation implementation of Bańbura, Giannone, and Reichlin (2010) . Setting φ = 500 (Minnesota limit) materially changes real-economy impulse responses — less persistent unemployment declines, more contractionary DM4 — confirming Pandemic Priors are necessary for this sample.

Q: What does cryptocurrency's macro role mean for monetary policy?

Central banks should incorporate cryptocurrency developments in inflation forecasting. Chen (2025) shows crypto shocks explain 18% of long-horizon PCE price-level forecast-error variance and produce a persistent 0.15% rise in the price level — a signature of demand-driven inflation rather than transitory financial noise. The contribution rises from 3.6% at 6 months to 17.6% at 30 months, while S&P 500, CRB, and FSI shocks combined contribute 10.1% at 30 months. Divisia M4 shows a contractionary response but insufficient to offset the price effect, suggesting monetary policy has been accommodative to crypto-driven inflation.

Q: Does the integration result hold beyond Bitcoin?

The current paper covers Bitcoin only, motivated by its dominant market capitalization during 2015–2024 and the need for a sufficiently long monthly time series for structural VAR identification. Bitcoin's market dominance averaged 40–65% of total cryptocurrency market cap over the sample, making the results descriptive of the overall market as well. Whether smaller cryptocurrencies, stablecoins, or DeFi tokens exhibit similar transmission mechanisms is an open empirical question. Main findings are robust to alternative variable orderings, price-level measures (CPI vs. PCE), and financial-stress indicators, suggesting the core result is not a Bitcoin-specific artifact.

Q: Does the cryptocurrency-macro spillover result extend to altcoins, DeFi protocols, or stablecoins?

Likely yes for altcoins (top-10 by market cap), more nuanced for DeFi, and structurally different for stablecoins — but the empirical evidence is sparse and a natural extension of Chen (2025) . Altcoins typically comove strongly with Bitcoin in return space, so the spillover pattern should replicate at smaller magnitudes; a natural extension applies the BSVAR with Bitcoin replaced by Ethereum or a market-cap-weighted top-10 index. DeFi protocols introduce additional channels — total value locked, governance token dynamics, liquidation cascades — that a price-only SVAR misses; the right extension would add aggregate DeFi TVL and a measure of leverage in lending protocols. Stablecoins are structurally different: their price shocks are small (depegging events are large but rare), and the relevant shock is the supply of stablecoins — a large stablecoin issuance amounts to mechanical T-bill demand, making the right framework closer to a money-supply shock in traditional monetary economics than a risk-asset price shock. Cross-country adoption rates vary enormously, so the U.S. results in Chen (2025) likely overstate the macro effect in low-adoption economies and understate it in high-adoption ones.

Q: What does cryptocurrency's 18% inflation variance contribution imply for monetary policy and CBDC design?

For monetary policy: the result implies that cryptocurrency markets have moved to a quantitatively significant input into the inflation process, and central banks should monitor crypto-driven financial conditions alongside traditional credit and equity measures. Chen (2025) documents that positive Bitcoin price shocks generate persistent inflationary pressure (a 0.15% rise in PCE), operating through wealth and investment channels familiar from the Bernanke-Blinder (1992) monetary transmission framework. The 18% long-horizon inflation variance contribution grows from 3.6% at 6 months to 17.6% at 30 months, making it the largest single non-own driver of price-level variance in this sample. Concrete implications: include crypto-driven financial conditions in monetary policy dashboards; recognize crypto wealth effects in consumption forecasting; distinguish sentiment-driven from technology-driven crypto shocks, since Chen (2025) finds sentiment shocks dominate and produce the inflation spillover. For financial regulators: prudential rules for bank crypto exposure and stablecoin reserve requirements need to account for the documented spillover magnitudes. The design implications for CBDC, if explored, would require a separate empirical framework beyond the scope of this paper.

Zhengyang Chen

July 2025

Abstract

This paper examines cryptocurrency shock transmission to financial markets and the macroeconomy using a Bayesian structural VAR with Pandemic Priors from 2015 to 2024. By affecting overall risk appetite, cryptocurrency price shocks generate positive financial market spillovers, accounting for 18% of equity and 27% of commodity price fluctuations. Real economic effects are significant in driving investment but remain limited, contributing only 4% to unemployment and 6% to industrial production variance. However, cryptocurrency shocks explain 18% of price-level forecast error variance at long horizons. Narrative analysis reveals sentiment and technology as primary shock drivers. These findings demonstrate cryptocurrency’s deep financial system integration with important inflation implications for monetary policy.

Type

Journal article

Publication

Journal of Risk and Financial Management

How Cryptocurrency Markets Now Drive Macroeconomic Outcomes

TL;DR: Cryptocurrency has crossed the threshold from isolated digital experiment to systemically important financial asset. Chen (2025, Journal of Risk and Financial Management) uses a Bayesian SVAR with Pandemic Priors to show that cryptocurrency price shocks explain 18% of equity, 27% of commodity, and 18% of long-horizon inflation variance over 2015–2024, with sentiment-driven shocks dominant and regulatory effects negligible. Real economic effects on industrial production and unemployment exist but are modest.

Key Concepts

Cryptocurrency-as-systematic-risk-factor: The empirical result that cryptocurrency now functions as a systematic source of variance in equity (17.7%) and commodity (27.2%) markets over 2015–2024, rather than a portfolio diversifier — evidence that cryptocurrency has crossed from isolated asset to systemically integrated risk factor. Chen (2025) .
Sentiment-dominant transmission: The finding that, across narrative-identified shock categories from 67 major crypto-market events (2014–2023), sentiment shocks (coefficient 1.36, t = 3.15) are the strongest driver of cryptocurrency price movements, with technology shocks second and regulatory shocks statistically insignificant. Chen (2025) .
Pandemic-prior cryptocurrency identification: The methodological adaptation of Cascaldi-Garcia (2022) Pandemic Priors — which extend the Minnesota prior with time dummies controlled by hyperparameter φ — to handle COVID-era extreme observations in a Bayesian SVAR identifying cryptocurrency macroeconomic transmission. Chen (2025) .

Three Views of Cryptocurrency’s Macroeconomic Role

Dimension	Diversifier view	Speculative-only view	Systematic-risk-factor view (Chen 2025)
Core claim	Crypto provides portfolio diversification due to low correlation with traditional assets.	Crypto is a speculative asset with no fundamental macroeconomic role.	Crypto has crossed into systemic importance with measurable spillovers to equity, commodity, and inflation variance.
Key references	Bouri et al. (2017) ; Charfeddine et al. (2020)	Early speculative-bubble literature	Chen (2025) , grounded in Baker & Wurgler (2007)
Empirical verdict	Diversification benefits weaken sharply during stress; crypto-equity comovements are positive, not negative, in 2015–2024.	Cannot explain the 17.7–27.2% equity/commodity variance contributions in modern data.	Supported. Variance decompositions show systemic transmission; narrative validation confirms sentiment and technology as drivers.
Policy implication	No special monetary or regulatory framework needed.	Monitor for fraud only; macroeconomic role irrelevant.	Central banks should monitor crypto for inflation pressure; financial regulators should treat it as a source of systemic risk.

Note: Diversifier view reflects pre-2018 literature. Chen (2025) covers January 2015 – November 2024.

Q1. Has cryptocurrency become a systematically important financial asset?

Yes. Chen (2025) finds that cryptocurrency price shocks explain 17.7% of S&P 500 forecast-error variance at 6 months and 27.2% of CRB commodity variance at 30 months — placing crypto alongside traditional macro shocks as a first-order driver of financial-market fluctuations.

This finding overturns the early-literature claim that cryptocurrency offers diversification benefits. Bouri et al. (2017) originally characterized Bitcoin as a hedge against global uncertainty, and Charfeddine, Benlagha, and Maouchi (2020) found weak, time-varying cross-correlations with conventional assets consistent with diversification. The 2015–2024 sample in Chen (2025) spans the institutional-adoption era — spot Bitcoin ETFs, corporate treasury holdings, derivatives integration — and yields the opposite conclusion: cryptocurrencies have become systematic risk amplifiers, aligned with the contagion-vs-interdependence distinction formalized by Forbes and Rigobon (2002) .

The empirical fingerprint is a drop in the Financial Stress Index on impact followed by recovery. This pattern — stress alleviates, not intensifies, with a positive crypto shock — is consistent with a risk-on channel operating through intermediary balance sheets, as described in Adrian and Shin (2010) and Brunnermeier and Pedersen (2009) . Crypto shocks also explain 5.7% rising to 8.2% of the Financial Stress Index variance, a modest but statistically meaningful share.

The scale of equity and commodity variance contributions (17.7% and 27.2%) is quantitatively comparable to the contributions of monetary policy and aggregate demand shocks in standard macro VARs, marking a structural break from the pre-2015 period when cryptocurrency had negligible macro spillovers.

Q2. What drives cryptocurrency price shocks — sentiment, technology, or regulation?

Sentiment dominates. Chen (2025) classifies 67 major crypto-market events from 2014–2023 into six categories and finds only sentiment shocks (coefficient 1.36, t = 3.15) and technology shocks (coefficient 1.02, t = 2.06) significantly explain the identified structural crypto-shock series. Regulatory, monetary, infrastructure, and network-effect shocks are all statistically insignificant.

The narrative identification follows Romer and Romer’s (2004) approach to monetary policy shocks, coding each event as +1 (favorable), −1 (unfavorable), or 0 (absent) in a given month. The six categories are: technology (protocol upgrades, hard forks, outages), sentiment (institutional adoption announcements, mainstream coverage, exchange collapses), regulatory (legal recognition, bans, enforcement), monetary (central bank moves affecting alternative-asset demand), infrastructure (exchange launches, custody solutions), and network effects (adoption milestones, integrations).

Sentiment dominance validates Baker and Wurgler’s (2007) investor-sentiment framework — retail-dominated asset markets exhibit amplified price movements beyond fundamentals. It partially contradicts papers like Borri and Shakhnov (2020) and Chokor and Alfieri (2021) that emphasize regulation as a primary driver: Chen (2025) finds regulatory event dummies are statistically insignificant after controlling for the full SVAR system.

The significant technology coefficient establishes that cryptocurrency is not a pure speculative bubble — protocol upgrades and technical improvements generate measurable economic value, consistent with Caporale, Gil-Alana, and Plastun (2018) , who documented persistence in the cryptocurrency market consistent with technology-based fundamentals.

Q3. How does cryptocurrency transmit to the real economy?

Through a dual channel: sentiment drives financial-market integration and technology drives real-economy effects. Chen (2025) documents that a one-standard-deviation positive Bitcoin price shock produces a sustained 1.2% rise in the S&P 500, a 2% rise in the CRB commodity index, a delayed 0.15% rise in industrial production, a persistent 0.02% decline in unemployment, and a 0.15% rise in the PCE price index over a 30-month horizon.

Two theoretical frames ground the financial-market response. Markowitz’s portfolio theory and Sharpe’s CAPM predict that assets with similar systematic risk exposures comove, which reframes cryptocurrency as an integrated risk asset rather than an isolated instrument. Behavioral extensions come from Baker and Wurgler’s (2007) investor-sentiment framework, where mood-driven trading creates systematic factors affecting all risky assets.

The real-economy transmission is quantitatively modest but theoretically well-grounded in investment-channel mechanics from Jermann and Quadrini (2012) and uncertainty-channel mechanics from Bloom (2009) , where asset-price volatility creates real-options effects on investment timing. The asymmetry between the large financial-market response (17.7–27.2% variance shares) and the modest real-economy response (6.2% industrial production, 3.8% unemployment at 30 months) reflects how each channel works: the financial-market response operates within days through correlated asset repricing and intermediary balance-sheet adjustments, while the real-economy response requires investment and hiring decisions with inherent multi-month lags.

Three empirical signatures distinguish the transmission mechanism:

Immediate: equity (+1.2%), commodities (+2%), financial stress drops on impact, then recovers.
Delayed but persistent: industrial production rises ~0.15% with a multi-month lag; unemployment falls ~0.02% persistently.
Cumulative inflation: the contribution of crypto shocks to price-level forecast-error variance grows from 3.6% at 6 months to 17.6% at 30 months — a signature of demand-side transmission, not transitory financial noise.

Q4. Why use Bayesian SVAR with Pandemic Priors for this question?

Standard VARs fail when the sample includes COVID-era extreme observations. Cascaldi-Garcia (2022) proposes extending the Minnesota prior with time dummies for the pandemic period, controlled by a hyperparameter φ that governs how much signal the model extracts from pandemic observations — as φ → 0 the pandemic period is treated as exceptional and its variance is absorbed by the dummies; as φ → ∞ the setup reverts to a conventional Minnesota prior.

Chen (2025) selects φ = 0.1 via marginal-likelihood maximization over a grid from 0.001 to 500, and shows that setting φ = 500 (the Minnesota-prior limit) produces materially different real-economy impulse responses — less persistent declines in unemployment and industrial production, more contractionary Divisia M4 movement. The data strongly favor the Pandemic Priors specification, confirming that how one handles COVID-19 observations affects the estimated transmission of cryptocurrency shocks to macroeconomic variables.

The monthly SVAR includes eight variables ordered recursively: PCE price index, unemployment rate, industrial production, Divisia M4, cryptocurrency price, S&P 500, CRB commodity index, and the St. Louis Fed Financial Stress Index. The prior follows the dummy-observation implementation from Bańbura, Giannone, and Reichlin (2010) , extended with Cascaldi-Garcia’s time-dummy block for the pandemic period. Overall tightness λ = 0.2; optimal φ selected by maximum marginal likelihood; impulse responses at 30-month horizon with 68% posterior probability bands.

Robustness checks confirm the main findings are stable under: alternative variable orderings (crypto ordered last produces virtually indistinguishable impulse responses); CPI instead of PCE for the price level; excess bond premium (Gilchrist and Zakrajšek 2012 ) or Cleveland Fed FSI instead of St. Louis FSI; and narrative validation via Romer-Romer-style event regression on six categories of crypto-market events.

Q5. What does cryptocurrency’s macro role mean for monetary policy?

Central banks should monitor cryptocurrency markets for demand-driven inflation pressure. With cryptocurrency shocks explaining 18% of long-horizon inflation variance, the asset class has crossed the threshold of monetary-policy relevance. Chen (2025) finds the contribution to PCE price-level forecast-error variance rises from 3.6% at 6 months to 17.6% at 30 months, while S&P 500, CRB, and Financial Stress Index shocks combined contribute 10.1% at 30 months — making cryptocurrency the largest single non-own driver of price-level variance in this sample.

The inflation mechanism matches New Keynesian demand-side transmission: positive crypto shocks raise equity and commodity prices, ease financial stress, stimulate investment and consumption, and pass through to aggregate-demand-driven inflation via the wealth channel (Case, Quigley, and Shiller 2005 ) and the financial-accelerator channel (Bernanke, Gertler, and Gilchrist 1999 ).

Divisia M4 shows initial expansion followed by contraction after a positive crypto shock — evidence of endogenous monetary tightening, but not aggressive enough to offset the price effect. Chen and Valcarcel (2021) argue Divisia aggregates are the correct monetary indicator when short rates are uninformative, and Chen and Valcarcel (2025) document their superior information content relative to simple-sum measures. The implication is that the Fed’s accommodative response leaves meaningful crypto-driven inflation in the system.

The demand-driven nature of the inflationary impulse distinguishes it from a transitory financial-market disturbance and makes it policy-actionable. Monetary authorities should incorporate cryptocurrency developments into their inflation forecasting models, and financial regulators should monitor the cryptocurrency market as a source of systematic risk given its substantial contribution to financial-market volatility.

Q6. Does the integration result hold beyond Bitcoin?

The current paper covers Bitcoin only. Bitcoin’s dominant market capitalization during 2015–2024 — averaging 40–65% of total cryptocurrency market cap over the sample — and the need for a sufficiently long monthly time series for structural VAR identification motivated this scope. Bitcoin’s market dominance makes the results broadly descriptive of the overall cryptocurrency market for this period.

Whether the results generalize to the full cryptocurrency ecosystem involves two open questions. First, altcoins, stablecoins, and DeFi tokens have different fundamental characteristics and may transmit to macro variables through different channels or with different magnitudes. Second, the cryptocurrency market structure changed substantially over the 2015–2024 window — from Bitcoin-dominated speculation to institutionally integrated infrastructure — and continuation samples will likely show evolving transmission dynamics as institutional adoption deepens further.

The paper’s main findings are robust to alternative variable orderings, price-level measures (CPI vs. PCE), and financial-stress indicators (excess bond premium vs. St. Louis FSI vs. Cleveland FSI), suggesting the Bitcoin-specific result is not an artifact of particular specification choices. Extending the framework to other cryptocurrency assets as data availability improves remains an important direction for future empirical work.

Q7. How do I estimate a Bayesian SVAR with Pandemic Priors for cryptocurrency shock analysis?

The setup combines a standard BVAR with Cascaldi-Garcia (2022) Pandemic Priors , which down-weight COVID-period observations to prevent them from contaminating impulse-response estimates while preserving the information they carry about volatility.

Chen (2025) implements this in five steps:

Construct a monthly panel of cryptocurrency price (Bitcoin), traditional financial market variables (equity, commodity prices, financial stress index), and macro variables (industrial production, unemployment, PCE).
Specify the BVAR with Minnesota-style shrinkage on the coefficients, plus Pandemic Priors that introduce additional shrinkage on COVID-period error variances (March 2020 through approximately mid-2021), using the dummy-observation implementation of Bańbura, Giannone, and Reichlin (2010) .
Identify cryptocurrency shocks via recursive ordering — crypto last among financial market variables but before macro real activity — and validate with Romer and Romer (2004) narrative identification matched against 67 documented crypto-market events.
Estimate via Gibbs sampling with overall tightness λ = 0.2; select the Pandemic Prior hyperparameter φ = 0.1 by marginal-likelihood maximization.
Report impulse responses with 16/84 credible bands and forecast error variance decompositions at 12-, 24-, 36-month horizons.

Why Pandemic Priors matter here: cryptocurrency markets experienced extreme volatility in March 2020 that would dominate a standard BVAR’s estimated dynamics. Setting φ = 500 (conventional Minnesota limit) materially changes real-economy impulse responses — less persistent unemployment declines, more contractionary Divisia M4 — confirming the priors are necessary for this sample.

Related questions: What cryptocurrency price series is appropriate for an SVAR? · How does narrative identification validate the recursive ordering?

Q8. Which cryptocurrency price and macro variables are appropriate for systemic-risk SVAR analysis?

For the cryptocurrency variable, Bitcoin’s log price is the standard choice given its dominant 40–65% market capitalization share during 2015–2024. Chen (2025) uses an eight-variable monthly SVAR ordered recursively: PCE price index, unemployment rate, industrial production, Divisia M4, Bitcoin price, S&P 500, CRB commodity index, and the St. Louis Fed Financial Stress Index.

Data sources:

Cryptocurrency prices: CoinMarketCap (daily, aggregated to monthly).
Traditional financial markets: S&P 500 and CRB commodity index from FRED ; OFR Financial Stress Index .
Macro variables: industrial production (INDPRO), unemployment (UNRATE), PCE (PCEPI) from FRED.
Monetary aggregate: Divisia M4 from CFS AMFM .
Sample period: January 2015 onward — earlier data has too little institutional adoption to identify the integrated regime.

Variable selection cautions: do not include trading volume in the SVAR (it breaks identification); do include a financial stress measure in addition to equity prices, as they capture distinct channels; for research on monetary-policy effects on crypto, add a policy indicator using Divisia M4 following Chen and Valcarcel (2021) .

Related questions: How are Pandemic Priors implemented? · Does the result hold if Bitcoin is replaced by Ethereum?

Q9. Does the cryptocurrency-macro spillover result extend to altcoins, DeFi protocols, or stablecoins?

Likely yes for altcoins, more nuanced for DeFi, and structurally different for stablecoins — but the empirical evidence is sparse and a natural extension of Chen (2025) .

Altcoins typically comove strongly with Bitcoin in return space, so the spillover pattern should replicate at smaller magnitudes. A natural extension applies the BSVAR with Bitcoin replaced by Ethereum or a market-cap-weighted top-10 index. Ethereum, with its DeFi infrastructure role, may show distinct dynamics that warrant separate identification.

DeFi protocols introduce additional channels — total value locked, governance token dynamics, liquidation cascades during stress — that a price-only SVAR misses. The right extension would add aggregate DeFi TVL and a measure of leverage in lending protocols.

Stablecoins are structurally different: their price shocks are small (depegging events are large but rare), and the relevant shock is the supply of stablecoins. A large stablecoin issuance amounts to mechanical T-bill demand — making the right framework closer to a money-supply shock in traditional monetary economics than a risk-asset price shock.

Cross-country considerations: cryptocurrency adoption rates vary enormously. The U.S. results in Chen (2025) likely overstate the macro effect in low-adoption economies and understate it in high-adoption ones.

Related questions: How does DeFi affect monetary transmission? · What are stablecoins’ systemic risk implications?

Q10. What does cryptocurrency’s 18% inflation variance contribution imply for monetary policy and financial regulators?

For monetary policy: the result implies that cryptocurrency markets have moved to a quantitatively significant input into the inflation process, and central banks should monitor crypto-driven financial conditions alongside traditional credit and equity measures. Chen (2025) documents that positive Bitcoin price shocks generate persistent inflationary pressure — a 0.15% rise in the PCE price level over a 30-month horizon — operating through wealth and investment channels. The 18% long-horizon inflation variance contribution grows from 3.6% at 6 months to 17.6% at 30 months, making cryptocurrency the largest single non-own driver of price-level variance in this sample.

Concrete implications for central-bank monitoring:

Include crypto-driven financial conditions in the dashboard. The OFR Financial Stress Index does not currently include crypto-specific volatility; an extension would improve real-time signal.
Recognize crypto wealth effects in consumption forecasting. With large retail crypto holdings, even modest wealth elasticities translate to first-order consumption effects.
Distinguish sentiment-driven from technology-driven crypto shocks. Chen (2025) finds sentiment shocks dominate and produce the inflation spillover; technology shocks are smaller in magnitude.

For financial regulators: prudential rules for bank crypto exposure, stablecoin reserve requirements, and stress-test scenarios all need to account for the documented spillover magnitudes. The demand-driven nature of the inflationary impulse — as opposed to a transitory financial-market disturbance — makes it policy-actionable rather than a noise term.

Related questions: What is the wealth-effect channel for cryptocurrency? · How does Divisia M4 respond to crypto shocks?

This paper situates cryptocurrency within Chen’s broader research program on monetary transmission and financial market integration. Chen (2026, Journal of Macroeconomics) examines how the Federal Reserve responds to financial conditions in setting policy — a transmission channel through which cryptocurrency-driven volatility could affect monetary decisions. Chen and Valcarcel (2021, JEDC) and Chen and Valcarcel (2025, JEDC) develop the structural VAR identification methods that this paper extends to cryptocurrency markets.

Data and Replication

Bitcoin price data: CoinMarketCap (daily, aggregated to monthly)
Macroeconomic series: FRED — PCE price index, CPI, unemployment, industrial production, S&P 500, CRB commodity index, St. Louis Fed FSI, Cleveland Fed FSI, excess bond premium
Divisia monetary aggregates: Center for Financial Stability — AMFM dataset , Divisia M4
Pandemic Priors implementation: Cascaldi-Garcia (2022) , φ = 0.1, λ = 0.2, 30-month impulse horizons, 68% posterior bands
Sample: Monthly, January 2015 – November 2024
Open access: UNI ScholarWorks · Journal of Risk and Financial Management

Citation

Chen, Zhengyang. 2025. “From Disruption to Integration: Cryptocurrency Prices, Financial Fluctuations, and Macroeconomy.” Journal of Risk and Financial Management 18(7): 360. https://doi.org/10.3390/jrfm18070360

@article{chen2025crypto,
  author    = {Chen, Zhengyang},
  title     = {From Disruption to Integration: Cryptocurrency Prices, Financial Fluctuations, and Macroeconomy},
  journal   = {Journal of Risk and Financial Management},
  volume    = {18},
  number    = {7},
  pages     = {360},
  year      = {2025},
  publisher = {MDPI},
  doi       = {10.3390/jrfm18070360},
  url       = {https://doi.org/10.3390/jrfm18070360},
  license   = {CC BY 4.0}
}